does monetary policy have an affect on financial stability?
Assessing-the-link-between-price-and-financial-stability_2015_Journal-of-Financial-Stability.pdf
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Journal of Financial Stability 16 (2015) 71–88
Contents lists available at ScienceDirect
Journal of Financial Stability
j o u r n a l h o m e p a g e : w w w . e l s e v i e r . c o m / l o c a t e / j f s t a b i l
ssessing the link between price and financial stability�
hristophe Blot a, Jérôme Creel a,b, Paul Hubert a,∗, Fabien Labondance a,c, rancesco Saraceno a,d
OFCE – Sciences Po, 69 Quai d’Orsay, 75340 Paris Cedex 7, France ESCP Europe, 79 Avenue de la République, 75011 Paris, France Université de Franche-Comté, CRESE, 30 Avenue de l’Observatoire, BP 1559, 25009 Besanç on Cedex, France SEP-LUISS, Viale Romania, 32, 00197 Roma, Italy
r t i c l e i n f o
rticle history: eceived 29 January 2014 eceived in revised form 22 July 2014 ccepted 11 December 2014 vailable online 19 December 2014
EL classification: 32 31 44
a b s t r a c t
This paper aims at investigating first, the (possibly time-varying) empirical relationship between price and financial stability, and second, the effects of some macro and policy variables on this relationship in the United States and the Eurozone. Three empirical methods are used to examine the relevance of A.J. Schwartz’s “conventional wisdom” that price stability would yield financial stability. Using simple correlations and VAR and Dynamic Conditional Correlations, we reject the hypotheses that price stability is positively correlated with financial stability and that the correlation is stable over time. The latter result and the analysis of the determinants of the link between price stability and financial stability cast some doubt on the appropriateness of the “leaning against the wind” monetary policy approach.
© 2014 Elsevier B.V. All rights reserved.
52
eywords: rice stability inancial stability CC-GARCH
s s
AR
. Introduction
Is financial stability correlated with price stability? This topical uestion matters for policy implementation, since most of the entral banks have become responsible for financial stability
� We thank the Editor, Iftekhar Hasan, two anonymous referees, Anne-Laure elatte, Elena Dumitrescu, Stephany Griffith-Jones, Jacques Le Cacheux, Grégory evieuge, Laurence Scialom, Francisco Serranito and participants at the 2013 FES- UD Annual Conference (Amsterdam), the 31st International Symposium on Money, anking and Finance (GdRE – Lyon), the 2014 Annual Congress of the French conomic Association (AFSE – Lyon), Journées d’économétrie appliquée à la macroé- onomie (MSH Paris Nord), the EconomiX seminar (Nanterre), the OFCE seminar Paris), the CATT seminar (Pau), for helpful suggestions and comments. All remaining rrors are ours. This research project benefited from funding of the European Union eventh Framework Program (FP7/2007-2013) under grant agreement no. 266800 FESSUD). ∗ Corresponding author. Tel.: +33 144185427.
E-mail addresses: [email protected] (C. Blot), [email protected] (J. Creel), [email protected] P. Hubert), [email protected] (F. Labondance), [email protected] (F. Saraceno).
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ttp://dx.doi.org/10.1016/j.jfs.2014.12.003 572-3089/© 2014 Elsevier B.V. All rights reserved.
upervision in the aftermath of the global financial crisis. In pite of the subject’s relevance, the literature on it is surprisingly imited, and mostly dominated by “conventional wisdom” on the inks between monetary and financial stability summarized by orio and Lowe (2002, p. 27): “A monetary regime that produces ggregate price stability will, as a by-product, tend to promote tability of the financial system”. The conventional wisdom orig- nates in Schwartz (1995), who emphasizes both a micro and a
acro channel in the link between inflation and asset prices. On he micro side, she relates price instability to inflation distortion, rowing uncertainty, shortened investment horizons, and gov- rnments’ nominal gains. All these dimensions produce financial nstability. On the macro side, she discusses the impact of price nstability on the value of collateral and on financial risk. Inflation
ould then encourage speculative investment, leading to financial nstability.
The link between financial and price stability is also relevant
or the ongoing theoretical debate on the conduct of monetary pol- cy, in particular on monetary policy instruments and objectives Smets, 2014; Woodford, 2012). Assuming that the conventional isdom is true, a central bank focusing on price stability would then
7 ancial
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lso contribute to financial stability (Bordo and Wheelock, 1998). lthough this conventional wisdom has not been explicitly adopted y central banks, it was de facto embedded in the conduct of mon- tary policy since the 1990s, which has been strongly influenced y the Jackson Hole Consensus stipulating that central banks are rimarily assigned the price stability objective and only implicitly he financial stability objective.1 The prevailing consensus in the iterature on central banks and monetary policy has indeed disre- arded the issue of financial instability.2 Following Bernanke and ertler (1999, 2001), asset prices had to be considered in mone-
ary policymaking only to the extent that they were threatening he price stability objective. The recent financial turmoil has cast ome doubt on these issues. The dotcom bubble and the subprime rises have indeed erupted in a context of low and stable inflation
the so-called “Great Moderation” – whereas the role of central anks in promoting price stability has been emphasized (Stock and atson, 2003, or more recently Mumtaz and Surico, 2012). Since
hen central banks have de facto or de jure given the financial sta- ility objective a status close to that of the price stability objective Cukierman, 2013).3 There is consequently a need for an in-depth nalysis of the link between price stability and financial stability. o our knowledge, there is no recent and comprehensive empirical ssessment of this link in the literature.4
The objective of this paper is to fill this gap and to investigate evi- ence on the link between price and financial stability since 1993 or the United States (US) and since 1999 for the Eurozone (EZ). It
ust be stressed that we do not address the issue of the causality ecause the conventional wisdom is compatible with several cau- ation approaches. The estimation period covers a stable period
the Great Moderation – as well as a more volatile period – the lobal Financial Crisis – which makes it possible to assess the effect f changing economic conditions on the empirical relevance of the onventional wisdom. Furthermore, covering the years between 993 (or 1999) and the Global Financial Crisis is all the more rele- ant since most central banks focused only on price stability during his period, despite a growing debate on the nexus between finan- ial and monetary stability (Borio and Lowe, 2002). The empirical pproach developed in this paper may then provide some critical nsights into the existing beliefs that prevailed de facto during the reat Moderation.
We test the null hypothesis that price stability is positively cor- elated with financial stability and that this relationship is stable ver time. This task is made difficult because there is no precise efinition of financial instability. One can distinguish at least two ecent approaches. First, Borio (2012) and Drehmann et al. (2012) eek to characterize financial cycles by using ad-hoc frequency- ased filters. The identification of financial cycles may be useful o characterize periods of boom and bust, but such an approach oes beyond what may be deemed financial instability. Second,
he indices of financial stability constructed by the ECB and the t Louis Fed can be used to give composite information on a wide ange of financial instruments. We adopt this second approach and
1 Financial stability here is understood in a narrow sense: central banks are meant o avoid a liquidity squeeze in the interbank market through their role as lenders of ast resort (LLR). Going a step further, Goodhart (2011) recalls that central banks have istorically pursued three objectives or functional roles: price stability, financial tability and support for State financing.
2 This issue is not dealt with in the influential papers of Clarida et al. (1999) or vensson (1999). 3 For instance, the Financial Services Act 2012 in the UK established a Financial
olicy Committee (FPC) and gave the Bank of England an explicit financial stability bjective. 4 Klomp and de Haan (2009) analyze the role of central banks in promoting nancial stability but they focus on central bank independence, invoking a political conomy dimension rather than the link through price stability.
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Stability 16 (2015) 71–88
ake use of both indices, plus asset price variables for robustness urposes.
The link between financial and price stability is analyzed hrough three different methods. We start with simple correlation nalysis – while unsophisticated, this has the merit of simplic- ty and clarity – using no statistical or theoretical manipulation f the data. We then test our hypothesis using a simple VAR odel, using as endogenous variables industrial production, infla-
ion, asset prices and various financial stability indicators. Finally, ollowing Engle (2002), we estimate a time-varying measure of orrelations based on dynamic conditional correlation (DCC). The hree methods provide converging results. We reject the hypothe- is that price stability is positively correlated with financial stability nd do not find evidence in support of the conventional wisdom. one of the three empirical methodologies shows a stable positive
ink between financial and price stability. Consequently, the main olicy implication of this paper is that, as the link between price and nancial stability is unstable and not positive, the “leaning against he wind” strategy is hard to justify on empirical grounds.
The rest of this paper is structured as follows. Section 2 presents he related literature. Section 3 describes the data and section 4 he empirical methodologies and the results. Section 5 investigates he determinants of the link between financial and price stabil- ty and discusses the appropriateness of the “leaning against the
ind” monetary approach in the Eurozone and the US. Section 6 oncludes.
. Related literature
.1. The conventional wisdom
The “conventional wisdom” (also known as the Schwartz ypothesis) is based on relatively few contributions. Besides the ork of Schwartz (1995), the idea that price and financial stability
xhibit a positive correlation is supported by Bordo et al. (2001) nd Issing (2003). Schwartz (1995) mainly focuses on the banking ector: “the fact remains that price instability undermines sound anking. It contributes to financial risk” (p. 39), and she goes beyond ebt-deflation à la Fisher (1933) as she relates the end of price hence financial) instability to sound monetary policy. Woodford 2012) also argues that monetary stability eliminates numerous ources of financial instability such as wage-price spirals. Nev- rtheless, to our knowledge, only a few papers are specifically edicated to an empirical assessment of the conventional wisdom. ordo and Wheelock (1998) and Bordo et al. (2001) conclude that nanticipated movements in the price level and inflation rate have ontributed historically to financial instability in the US, ever more o between 1870 and 1933, or in the 1980s and 1990s. Further- ore, Hardy and Pazarbasioglu (1999) and Dermirguc-Kunt and etragiache (1997) find that countries with high levels of inflation re more prone to financial crises.
Before the global financial crisis, the conventional wisdom had lready come in for criticism, e.g. by Borio and Lowe (2002), ajan (2005), White (2006) and Leijonhufvud (2007). These authors laimed that monetary stability could lead to financial instability in hat it sometimes allows low interest rates (“cheap money”), favor- ng projects with a high level of risk. The argument is also raised by aylor (2009), who presents a counterfactual dynamic of housing arket prices from 2001 to 2006. He argues that if monetary policy
ates had not been excessively low, with regard to what is implied
y a Taylor rule, the housing boom would have been avoided and o bust would have occurred. These different authors also point ut that major economic and financial crises were not preceded by nflationary pressures. This is the “paradox of credibility” according
ancial
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o which central banks have gained credibility in curbing inflation, hich has ultimately led to an increase in the vulnerability of the nancial system and then to financial instability. It therefore seems hat inflation is not a good predictor of banking or financial crises.
.2. Theoretical linkages between price and financial stability
In her seminal work, Schwartz (1995) relates price instability o financial instability through inflation distortions, on one side, nd collateral value and increased financial risk, on the other side. ordo and Wheelock (1998) find no specific mechanism explain-
ng the conventional wisdom: on the one hand, financial instability ay result from monetary disturbances, if the unexpected infla-
ion resulting from monetary contractions or expansions leads to anking panics. On the other hand, the correlation between finan- ial and price stability may also be the consequence of financial ragility when, in periods of economic boom, confidence improves nd leverage increases, leading to over-indebtedness. Asset prices lso increase, but not necessarily the price of goods and services. f inflation increases, it may even inflate the bubble, as it leads o a decrease in the real cost of borrowing. The process ends hen agents are unable to repay their debt because of a negative
xogenous shock or a tightening of monetary policy. The ensuing ebt-deflation process leads to price and financial instability fuel-
ng each other. In a similar vein, Adrian and Shin (2009) and Rajan 2005) suggest that, with low inflation, the search for high yields eads to a rise in risk-taking.
Financial instability may have a direct effect on the level of eco- omic activity, and on price stability, through different channels. ilchrist and Leahy (2002) identify a wealth effect as, during asset rice booms, wealthier agents consume more and increased con- umption has a direct and positive impact on inflation. This channel lso works in the other way: in periods of high financial stress, hen asset prices drop, economic agents are more constrained and
end to consume less. A similar channel can be identified via Tobin’s theory of investment. During periods of financial stress, firms re less likely to find financing sources, and therefore invest less. inally, the financial accelerator of Bernanke and Gertler (1989) lso plays a role. A financial instability shock induces a fall in asset rices that deteriorates the balance sheets of economic agents nd their net worth. Agents are less likely to borrow and thus to nvest. This situation leads to a vicious cycle, the financial accelera- or, of decreasing asset prices, tightening financing conditions, and eclining economic activity and prices.
.3. Implications in terms of policy strategies
The (assumed positive) correlation between price and financial tability has become a crucial issue for monetary policy. Some crit- cs of the conventional wisdom argued that, in addition to their ole as LLR, central banks should also be given the task of seeking financial stability”. These discussions are related to the Tinbergen rinciple postulating that N instruments are needed to achieve N bjectives. This branch of the literature is abundant (see Disyatat, 010), but it does not seriously challenge the “conventional wis- om”. Indeed, Blanchard et al. (2010) explain that no change is equired in the policy reaction function, except better coopera- ion with the supervisory body. Woodford (2012) proposes that the entral bank should embrace a flexible inflation targeting strategy, hile White (2009) calls for a “leaning against the wind policy”.
At least three views on the relationship between financial stabil-
ty and monetary policy (then price stability via monetary policy) an be found in the literature (Smets, 2014): a modified Jackson ole consensus in the vein of Blanchard et al. (2010), where cen-
ral banks still primarily focus on price stability, whereas financial
a f n r
Stability 16 (2015) 71–88 73
tability is tackled with an additional instrument – the macropru- ential tool; Brunnermeier and Sannikov’s (2014) intermediation heory of money, arguing that financial and price stability cannot e distinguished, so that monetary policy should aim at stabilizing he macro-financial environment and should be strongly coordi- ated with financial stability policy; and the “leaning against the ind” approach of White (2009) and Woodford (2012).
We focus our discussion on the last view, as the empirical nalysis below allows us to assess its policy relevance. Woodford 2012) builds a simple New Keynesian model in which financial rictions, identified with the spread between safe and risky bor- owers, reduce the average marginal utility of income, for a given evel of real activity. Thus, larger credit frictions impact both the S curve (reducing aggregate demand for given inflation), and the hillips curve (increasing inflationary pressures for given levels of he output gap). Financial frictions may increase with an endoge- ous probability, which is increasing with the level of leverage f the economy; the latter in turn is positively related, via the evel of intermediation, to the output gap. With completely exoge- ous credit frictions, it is possible to show that inflation-targeting emains the optimal strategy for central banks, and that credit rictions play the same role as cost-push shocks: increasing finan- ial instability yields inflationary pressure, and requires the central ank to increase interest rates to stabilize prices.
Woodford then shows that when the probability of crises is ndogenous, and related to the level of leverage in the economy, exible inflation-targeting remains the optimal monetary policy trategy. Nevertheless, if the risk of financial crisis increases beyond
certain threshold, then it may be optimal for the central bank to lean against the credit boom”, increasing rates beyond the level hat would be required by the macroeconomic variables. As a con- equence, the central bank could be led to undershoot both the nflation rate and the output gap objectives.
While Woodford acknowledges that the spread between his tylized model and practical guidelines for central bank action emains wide, his paper highlights the theoretical channel between nancial stability and price stability, which mostly goes through n augmented version of the Phillips curve. To summarize, Wood- ord concludes from his analysis that (a) monetary policy impacts nancial and price stability in the same direction, thus lending sup- ort to the conventional wisdom; this is especially true in normal imes, when the impact of financial crisis probabilities on the con- uct of monetary policy is negligible; and (b) that when the risk f financial crisis increases substantially, it may become optimal o undershoot the inflation objective (i.e. so whenever facing the isk of financial instability, it is better to err on the restrictive side). nly in situations of high risk does a possible conflict between the
wo objectives arise, which in turn calls for macroprudential policy o take care of the objective of financial stability, while the cen- ral banks remain focused on price stability. Woodford’s model, herefore, reaches the conclusion that standard inflation-targeting trategies are only exceptionally altered by the possibility of finan- ial instability, and that the latter problem is best dealt with by ppropriate regulation.
Gali (2014) reaches a different conclusion. In a rational- xpectations setting, he argues that a bubble has two different omponents that react differently to a change in short-term nterest rates: the fundamental component and the bubble (or elf-fulfilling) component. The fundamental component clearly onfirms the usefulness of the “leaning against the wind” mone- ary policy: a higher nominal short-term interest rate will dampen
ggregate demand. The bubble component requires dampening uture aggregate demand; hence it requires a lower short-term ominal interest rate. The optimal monetary policy depends on the elative size of the bubble component vis-à-vis the fundamental
7 ancial Stability 16 (2015) 71–88
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Table 1 Data description.
Variable Definition Source
us cpi Consumer Price Index for All Urban Consumers: All Items
FRED
us pgdp Gross Domestic Product: Implicit Price Deflator monthly interpolated (linear match)
FRED
us fsi St. Louis Fed Financial Stress Index FRED us hous Median Sales Price for New Houses
Sold in the United States FRED
us stock S&P 500 Stock Price Index FRED us loan Loans and Leases in Bank Credit, All
Commercial Banks FRED
us m Money Zero Maturity – Money Stock FRED us indpro Industrial Production Index FRED us cbrate Effective Federal Funds Rate FRED us bonds 10-Year Treasury Constant Maturity
Interest Rate FRED
us rbonds Real 10-Year Treasury Constant Maturity Interest Rate
Authors’ computation
ez cpi Euro area HICP – Overall index ECB ez pgdp Gross Domestic Product Deflator for
the Euro Area, monthly interpolated (linear match)
ECB
ez fsi Euro area CISS, Systemic Stress Composite Indicator.
ECB
ez hous Euro area, Residential property prices, New and existing dwellings; Residential property in good & poor condition; Whole country
ECB
ez stock Dow Jones Euro Stoxx 50 Price Index – Historical close, average of observations through period
ECB
ez loan Euro area, Monetary and Financial Institutions (MFIs) reporting sector-Loans, Total maturity, Non-Financial corporations (S.11) sector
ECB
ez m M3 for the Euro Area ECB ez indpro Euro area Industrial Production Index,
Total Industry (excluding construction) ECB
ez cbrate Main refinancing operations interest rate
ECB
ez bonds Long-Term Government Bond Yields: 10-year: interest rate Main (Including Benchmark) for the Euro Area
ECB
ez rbonds Real Long-Term Government Bond Yields: 10-year interest rate
Authors’ computation
oil Spot Oil Price: West Texas FRED
o t
l t e
4 C. Blot et al. / Journal of Fin
ne. While his model does not incorporate credit or financial fric- ions, Gali warns against a “leaning against the wind” policy, and dvocates further research on macroprudential policies.
. Data
Our data set focuses on price and financial stability variables or the United States and the Eurozone over a period charac- erized by the “Great Moderation” and by the “Global Financial risis”. We use monthly samples: 1993M12-2012M12 for the US nd 1999M01-2012M12 for the EZ. The sample lengths are limited y the availability of financial stability indices. But this limitation llows focusing specifically on the link between price and finan- ial stability during a period (from the beginning of the 1990s ntil 2007) when it was believed that the monetary regime had ontributed to price stability, and by the same token to financial tability (Benati and Goodhart, 2010).5
As a measure of price stability, we alternatively use the con- umer price index (CPI) and the GDP deflator (PGDP) in the US and n the EZ. The measure of financial stability is more controversial Allen and Wood, 2006), because it is a polymorphous concept that
ay be related to the volatility of some asset prices, to the financial onditions of financial institutions or to the ability of the financial ystem to deal with shocks. No consensus has clearly emerged so ar to provide a definition. In this paper we use the financial stabil- ty indicators constructed by the Federal Reserve of St Louis for the S and by the ECB for the EZ.
The St Louis financial stress index (STLFSI) measures the degree f financial stress in the markets and is constructed from 18 weekly ata series: seven interest rate series, six yield spreads and five ther indicators. Each of these variables captures some aspect of nancial instability. Accordingly, as the level of financial instabil-
ty in the economy evolves, the 18 data series are likely to move ogether.6 The main assumption in the construction of this index s that financial stress is the most important factor in explaining he co-movement of these variables. Using a principal compo- ents analysis, it identifies this factor. The average value of the TLFSI is designed to be zero. Thus, zero represents normal finan- ial market conditions. Values below zero suggest below-average nancial market stress, while values above zero suggest above- verage financial market stress.
The ECB’s composite indicator of systemic stress (CISS) includes 5 raw, mainly market-based financial stress measures. These are plit equally into five categories, namely the financial intermedi- ries sector, money markets, equity markets, bond markets and oreign exchange markets.7 The CISS thus places relatively more eight on situations in which stress prevails simultaneously in sev-
ral market segments. It is unit-free and constrained to lie within he interval [0,1]. Further details are given in Hollo et al. (2012).
The STLFSI and the CISS measure financial instability in the US nd the EZ, but one may argue that their methodology is different
nd that they do not capture exactly the same concepts. Kliesen t al. (2012) classify the STLFSI as a Financial stress index and the CISS s a Financial conditions index, because the latter is constructed not
5 The description of the monetary regime since the early 1990s goes beyond the cope of this paper. See Bordo and Schwartz (1999) and Benati and Goodhart (2010) or historical detailed descriptions of the different monetary regimes.
6 The latest STLFSI press release can be found at http://www.stlouisfed. rg/newsroom/financial-stress-index. For more details on the construction of the TLFSI, see the Appendix to the January 2010 issue of the St. Louis Fed’s National conomic Trends. 7 The CISS index can be found at http://sdw.ecb.europa.eu/browse.do?node=
551138.
C b fi t
v F t T
Intermediate
nly with financial data but also with economic data. Nevertheless, hese indices are highly correlated.8
This is reassuring because they are designed to measure simi- ar effects, such as shocks that occur in financial markets and are ransmitted to the real economy, or shocks that appear in the real conomy and are propagated to the financial markets. Even if the ISS is composed with economic data, the dimensions measured y these data are strongly linked with the financial sector. As the nancial data in the CISS are very similar to those used in the STLFSI, hese indices are strongly alike.
Beyond the STLFSI and CISS, we also use other macroeconomic ariables in our VAR and DCC specifications. All variables, except SI, are in year-over-year growth rates. Table 1 presents the defini- ions and sources. Fig. 1 plots price and financial stability data, and able 2 presents descriptive statistics.
8 Table A in the Appendix lists the constituents of each index.
C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88 75
Fig. 1. Da
Table 2 Descriptive statistics.
Variable Obs Mean Std. Dev. Min Max
us cpi 229 2.48 1.13 −1.99 5.53 us pgdp 229 1.99 0.66 0.22 3.38 us fsi 229 0.03 1.00 −1.32 5.49 us hous 229 3.63 6.11 −14.51 18.08 us stock 229 5.15 17.76 −42.27 48.75 us loan 229 4.08 4.13 −10.89 10.55 us m 229 4.92 5.06 −5.96 19.28 us indpro 229 2.25 4.58 −15.15 8.73 us cbrate 229 3.21 2.23 0.07 6.54 us bonds 229 4.73 1.44 1.53 7.96 us rbonds 229 2.25 1.64 −1.92 5.55 ez cpi 168 2.07 0.77 −0.60 4.00 ez pgdp 168 1.74 0.57 0.57 2.82 ez fsi 168 0.22 0.18 0.04 0.78 ez hous 168 3.86 3.33 −4.36 7.52 ez stock 168 1.19 23.38 −45.12 50.87 ez loan 168 5.64 5.22 −3.92 15.11 ez m 168 5.95 3.53 −2.07 12.62 ez indpro 168 0.70 5.60 −21.44 9.05 ez cbrate 168 2.52 1.19 0.75 4.75 ez bonds 168 4.25 0.68 2.10 5.70
4
t a w t a o
o s i v t c b a t a h r s m p a a F t a c s v i v f
t 2 s modity futures (Silvennoinen and Thorp, 2013) and to commodity
ez rbonds 168 2.18 1.00 −0.19 4.69 oil 229 11.34 34.05 −58.97 136.76
. Identifying the link between price and financial stability
We assess the link between price and financial stability through hree methods: simple correlation, Vector AutoRegression (VAR) nd dynamic conditional correlations (DCC). As the conventional isdom does not provide any clear guidance on any structural rela-
ion between financial and price stability, these methods appear ppropriate, as they focus on different statistical representations f the link between the two variables of interest and do not rely
p a b
ta.
n specific theoretical foundations. The first method looks at the imple static correlation between levels of the two variables of nterest. The second assesses how exogenous shocks to one of the ariables of interest affect the level of the other. It adds informa- ion, relative to the simple correlation analysis, as VAR analysis an be used to take into account the past dynamics of price sta- ility and financial stability and to identify shocks. These shocks re orthogonal to macro variables (industrial production, infla- ion and the central bank interest rate) and to variables possibly ffecting price and financial stability (loans, monetary aggregate, ousing prices and stock market prices). We therefore assess the esponse of financial stability (respectively, price stability) to a hock on price stability (respectively, price stability). The third ethod investigates the dynamic conditional correlation between
rice and financial stability based on the estimation of the two vari- bles’ conditional variances. This method presents two additional dvantages relative to the static correlation and VAR analyses. irst, the approach is time-varying, which improves the informa- ion relative to a static correlation approach. By construction, it ccounts for the possibility that the link between price and finan- ial stability may change over time. This is of paramount interest ince, according to the “conventional view”, the reduction in the olatility of inflation should have coincided with financial stabil- ty. Second, the approach is based on an estimate of the conditional olatility resulting from the GARCH model within a multivariate ramework.
The DCC approach has been widely used in recent papers inves- igating notably the linkages between bond prices (Antonakakis, 012), stock prices (Cai et al., 2009 or Bali and Engle, 2010), and tock and bond prices (Yang et al., 2009), with an extension to com-
rices (Creti et al., 2013). Though Cai et al. and Yang et al. take into ccount the inflation environment, they do not study the linkages etween financial and consumer prices per se.
76 C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88
l smo
4
r i p p E w s E i p f t
o e n
4
t t p c
T C
N
Fig. 2. Linear fit and Epanechnikov–Kerne
.1. Simple correlation
We first address our research question by computing cor- elation coefficients between inflation and financial stability ndicators. Correlations are measured here for the whole sam- le and are presented in Table 3. Fig. 2 shows scatterplots of rice and financial stability variables together with linear fit and panechnikov–Kernel smoothing lines. Whereas the conventional isdom assumes a positive correlation between price and financial
tability, we do not find such a result in our data. Results for the urozone show a negative correlation coefficient that is not signif-
cant with CPI, suggesting the absence of a relationship between rice and financial stability in Europe since 1999. The correlation is ound to be negative and statistically significant for the GDP defla- or. The results for the United States are also inconclusive in terms
i i o o
able 3 orrelation pairs.
us fsi us cpi us pgdp
us fsi 1 us cpi −0.32(0.00) 1 us pgdp −0.34(0.00) 0.93(0.00) 1 N 229
ote: Significance level of each correlation coefficient in parenthesis.
othing lines (with 95% confidence bands).
f the conventional wisdom. They suggest that prices, measured ither by the CPI or GDP deflator, and financial stability are either ot or negatively correlated.
.2. VAR
Our second exercise uses a VAR model estimate for the US and he EZ. We estimate a vector of 8 endogenous variables ordered in he following way: house prices, industrial production, consumer rice index, loans to the non-financial sector, money supply, main entral banks’ interest rate, stock markets and the financial stabil-
ty index [HOUS, INDPRO, CPI, LOAN, M, CBRATE, STOCK, FSI]. The dentification of shocks is based on Cholesky decomposition. The rdering of the variables is supposed to mimic the speed of reaction f each series. Financial market variables are supposed to react the
ez fsi ez cpi ez pgdp
ez fsi 1 ez cpi −0.05(0.52) 1 ez pgdp −0.28(0.00) 0.39(0.00) 1 N 168
C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88 77
. 3. IR
f a i t C t k
o e fi
Fig
astest and macro variables the slowest. House prices are peculiar, financial variable that adjusts slowly, notably because the price s not set daily on an organized market. Ultimately what matters
he most to test our null hypothesis is the relative position of the PI (or PGDP) and of the FSI, and it seems reasonable to assume hat the FSI, which captures asset prices set daily on financial mar- ets, reacts more quickly than the CPI. Moreover, we include some
i t e m
Fs.
f the constituents of the financial stability index in the vector of ndogenous variables in order to single out the most exogenous nancial shocks orthogonal to housing or asset prices. However, as
t could be argued that these constituents should not be included as hey make the interpretation of the shocks more difficult, we also stimate our VAR model without the FSI constituting variables. Esti- ations are performed with 3 lags. The VAR model enables to take
7 ancial
i c fi F t V
o i r
h W s T i i
N
8 C. Blot et al. / Journal of Fin
nto account the past dynamics of each variable when assessing the orrelation between price and financial stability. Hence, shocks to nancial stability are interpreted as the unexpected component of SI once the past dynamics of all the variables from the VAR and he current unexpected shocks on the other seven variables of the AR have been taken into account.
As the focus of the paper is on the effect of financial stability n price stability and vice versa, Fig. 3 provides the corresponding mpulse response functions (IRF) in both the US and the EZ. The esults in the US are significantly asymmetric. Indeed, on the one
i T i i
Fig. 4. Dynamic conditi
ote: Constant lines represent the average of the dynamic correlations.
Stability 16 (2015) 71–88
and an inflationary shock in the US increases financial instability. e isolate a positive link in this direction, which would be con-
istent with the macro side channel of the conventional wisdom. he impact is significant for more than 12 months when the shock s measured by CPI inflation and only for a few months when it s measured by the GDP deflator. On the other hand, a financial
nstability shock reduces inflation. Here the link is then negative. he shock on the financial stability index might reflect an increase n financial fragility or a financial crisis leading to a reduction of nflation and, in the worst case, to a debt-deflation process. The
onal correlations.
C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88 79
(Conti
r fi E t i
t t D e c i
4
v b b c l
Fig. 4.
esults thus show evidence of a positive and a negative link between nancial instability and price stability in the US. The results in the urozone indicate the same asymmetry, although the response of he financial stability variable to a shock to the GDP deflator is nsignificant.
The IRF are also interesting as they show that a negative infla- ion shock has a positive effect on the FSI. This result can be related o the argument suggested by Rajan (2005) or Leijonhufvud (2007).
uring periods of low inflation and low interest rates, investors are ager to find high returns. This leads to the development of finan- ial innovations, potentially riskier, and is conducive to financial nstability.
c a b p
nued).
.3. Dynamic conditional correlations
The two previous methods failed to lend support to the con- entional wisdom, in that no clear positive relationship emerges etween indicators of price stability and indicators of financial sta- ility. This could be due to the length of the time span that we onsidered (almost two decades for the United States, and slightly ess for the Eurozone). Indeed, the existence of structural breaks
ould affect the results. Therefore, it is certainly worth resorting to
time-varying analysis of correlation to assess whether there have een sub-periods over which the conventional wisdom can be sup- orted by data. To identify the possibly time-varying relationship
80 C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88
(Conti
b m t c
c o ε
⎧⎨ ⎩
w t i a d t CPI inflation and the financial stability index, the matrix is simply:
Fig. 4.
etween price and financial stability, we estimate a time-varying easure of correlation based on the dynamic conditional correla-
ion (DCC) multivariate GARCH model of Engle (2002), in which the onditional correlation follows a GARCH(1,1) process.
The multivariate GARCH model is a specification of both the onditional mean and the conditional variance, where the variance f the residuals εt is a function of prior unanticipated innovations 2 t and prior conditional variances �
2 t . It is written as follows:
Yt = ˇ.Xt−1 + ∈t ∈t = H1/2t · vt Ht = D1/2t Rt D
1/2 t
D
nued).
here Yt is the vector of dependent variables (here CPI infla- ion and the financial stability index), Xt−1 is the vector of ndependent variables, which contains lags of dependent vari- bles and vt is a vector of normal, independent and identically istributed innovations. Dt is the diagonal matrix of condi- ional variances. In the bivariate case of the model describing
t = (
�21,t 0 0 �22,t
)
C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88 81
(Conti
m
�
R
a r{
Fig. 4.
Each conditional variance evolves according to a GARCH(1,1) odel:
2 i,t
= �0 + �1 · �2i,t−1 + �2∈ 2 i,t−1
Rt stands for the matrix of quasi-correlations:
t = (
1 �21,t �12,t 1
) w u c m
a
nued).
nd the conditional quasi-correlations are given by the following elation:
Rt = diag(Qt )−1/2 · Qt · diag(Qt )−1/2 Qt = (1 − �1 − �2)R + �1(ε̃t−1 · ε̃
′ t−1) + �2 · Qt−1
here R is the unconditional covariance of the standardized resid- als ε̃t . � 1 and � 2 are parameters, governing the dynamic of
onditional correlations, to be estimated. If � 1 = 0 and � 2 = 0, the odel boils down to a constant conditional correlation model. The DCC-GARCH model (see Engle, 2002) can be viewed as
multivariate representation of a univariate GARCH process in
82 C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88
Fig. 5. Robustness – linear fit and Epanechnikov–Kernel smoothing lines (with 95% confidence bands).
w T t d t a o a r t c c
fi
1
Table 4 DCC quasi-correlation coefficients.
Variable Coef Robust SE p-value
US CPI – FSI (model 1) −0.30 0.74 0.68 PGDP – FSI (model 1) −0.44 0.16 0.01 CPI – FSI (model 2) −0.17 0.16 0.28 PGDP – FSI (model 2) −0.45 0.17 0.01 CPI – FSI (model 3) −0.05 0.25 0.85 PGDP – FSI (model 3) −0.61 0.22 0.01 CPI – FSI (model 4) −0.06 0.18 0.72 PGDP – FSI (model 4) −0.46 0.15 0.00
EZ CPI – FSI (model 1) 0.19 0.15 0.21 PGDP – FSI (model 1) 0.63 0.13 0.00 CPI – FSI (model 2) 0.05 0.16 0.74 PGDP – FSI (model 2) −0.17 0.15 0.25 CPI – FSI (model 3) 0.25 0.15 0.10 PGDP – FSI (model 3) −0.25 0.19 0.19 CPI – FSI (model 4) −0.22 0.15 0.13 PGDP – FSI (model 4) 0.05 0.15 0.72
hich dynamic covariance is computed from conditional variance. he procedure involves two steps: first, estimating the condi- ional volatility of each individual series and, second, capturing ynamics in the covariance of the standardized residuals from he first stage procedure and using them as inputs to estimate
time-varying correlation matrix. When interpreting the results, ne has to keep in mind that the DCC matrix is a weighted aver- ge of the unconditional covariance matrix of the standardized esiduals, and of parameters that govern the dynamics of condi- ional quasi-correlations. The DCC matrix is not the unconditional orrelation matrix, and for this reason it is generally labeled “quasi- orrelations” (see Aielli, 2013; Engle, 2009).
We estimate four different DCC-GARCH models for inflation and nancial stability:
. A specification with a constant only and a dummy for the global financial crisis. Here financial stability and inflation are there- fore determined by a constant term. It is the most parsimonious
model. For the equation explaining inflation, this boils down to the case where inflation is equal to a target plus an error term. There is no link between price and financial stability except in the variance-covariance matrix.
N w m
ote: Dynamic conditional correlation multivariate GARCH models are estimated ith the Huber-White estimator so standard errors are robust to some types of isspecification.
C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88 83
ustne
N
2
3
4
l v i t b c f c m
n d b t 1
i i t v r a a
Fig. 6. Rob
ote: Dotted lines represent 1 and 2 SE confidence bands.
. A specification including lags of potential components of finan- cial instability: housing prices, stock market prices, volumes of loans to the private sector in the vein of Bordo et al. (2001).
. A specification including policy variables: the central bank inter- est rate and the monetary aggregate.
. A specification including all the variables of models 2 and 3.
Though the aim of this approach is to provide dynamic corre- ations, the constant quasi-correlation coefficients of conditional ariances give a first picture of the relation between the volatil- ty of price and the volatility of the FSI, which may be compared o simple correlations. They are shown in Table 4. The results are roadly in line with simple correlation coefficients. In the US, quasi-
orrelation coefficients are negative, but not statistically significant or the CPI. In the case of the Eurozone, the results are even less lear-cut. Quasi-correlations are sometimes positive (3 out of 4 odels for the CPI and 2 out of 4 for the PGDP) and sometimes
c b a M
ss – IRFs.
egative. These coefficients are nevertheless rarely significantly ifferent from zero. The only exception is the quasi-correlation etween the PGDP and FSI in the first model (significantly posi- ive) and the CPI and FSI in model 3, also positive but only at the 0% threshold.
The dynamic correlations for each specification and for the two ndicators of inflation are plotted in Fig. 4. The solid constant line s the average of the dynamic correlations. These results indicate hat the correlation between financial and price stability is highly olatile over the sample and does not present any stable empirical egularity. It can be either positive or negative for several months, nd then rapidly switch sign. This is true both in the United States nd in the Eurozone, and regardless of the model considered. The
onventional wisdom, according to which price and financial sta- ility go hand in hand, is clearly not confirmed by the DCC empirical nalysis, at least over the two periods considered here: the Great oderation and the Global Financial Crisis. As a consequence, it is
84 C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88
N
T C
N
Fig. 7. Robustne
ote: Constant lines represent the average of the dynamic correlations.
able 5 orrelation pairs.
us stock us cpi us pgdp
us stock 1 us cpi −0.31(0.00) 1 us pgdp −0.31(0.00) 0.93(0.00) 1 N 229
ote: Significance level of each correlation coefficient in parenthesis.
ss – DCC.
ez stock ez cpi ez pgdp
ez stock 1 ez cpi −0.17(0.01) 1 ez pgdp −0.44(0.00) 0.39(0.00) 1 N 168
C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88 85
Table 6 Determinants of DCC.
dcc us fsi cpi 1 dcc us fsi cpi 2 dcc us fsi cpi 3 dcc us fsi cpi 4
OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS
us fsi 0.19*** 0.22*** 0.09* 0.10 0.10* 0.11** 0.19*** 0.21***
[0.05] [0.07] [0.05] [0.06] [0.05] [0.06] [0.04] [0.08] us cpi 0.17*** 0.16 0.18*** 0.16* 0.16*** 0.16* 0.13*** 0.12*
[0.04] [0.10] [0.04] [0.10] [0.03] [0.09] [0.03] [0.06] us cbrate 0.10*** 0.11*** 0.11** 0.04 0.05 0.05 0.02 0.03 0.03 0.01 0.02 0.01
[0.03] [0.03] [0.05] [0.03] [0.03] [0.05] [0.03] [0.03] [0.05] [0.02] [0.02] [0.05] us m 0.02** 0.02** 0.02 0.03*** 0.03*** 0.03* 0.06*** 0.06*** 0.06*** 0.03*** 0.04*** 0.04***
[0.01] [0.01] [0.02] [0.01] [0.01] [0.02] [0.01] [0.01] [0.01] [0.01] [0.01] [0.01] us indpro 0.03** 0.01 0.03 0.03** 0.02** 0.03* 0.04*** 0.03*** 0.04** 0.04*** 0.02** 0.04***
[0.01] [0.01] [0.02] [0.01] [0.01] [0.02] [0.01] [0.01] [0.02] [0.01] [0.01] [0.02] crisis 0.2 0.19 0.21 0.35** 0.25* 0.35 0.05 −0.03 0.07 −0.16 −0.13 −0.15
[0.16] [0.15] [0.24] [0.16] [0.14] [0.23] [0.16] [0.15] [0.25] [0.13] [0.12] [0.22] cons −1.09*** −0.66*** −1.09*** −1.07*** −0.58*** −1.06*** −0.89*** −0.46*** −0.93** −0.66*** −0.34*** −0.68**
[0.19] [0.15] [0.37] [0.18] [0.13] [0.34] [0.18] [0.14] [0.37] [0.14] [0.11] [0.28]
N 229 229 227 229 229 227 229 229 227 229 229 227 R2 0.22 0.11 0.22 0.15 0.05 0.15 0.26 0.18 0.26 0.25 0.13 0.25
dcc ez fsi cpi 1 dcc ez fsi cpi 2 dcc ez fsi cpi 3 dcc ez fsi cpi 4
OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS
ez fsi 1.46*** 1.52 1.48*** 1.23 1.32*** 1.20 0.97** 1.21 [0.45] [1.04] [0.49] [1.15] [0.50] [0.77] [0.46] [0.75]
ez cpi 0.12* 0.17 −0.17** −0.22 0.29*** 0.36** 0.02 −0.03 [0.07] [0.12] [0.08] [0.16] [0.08] [0.18] [0.07] [0.12]
ez cbrate 0.03 0.11** 0.05 −0.06 0.00 −0.07 −0.14** −0.05 −0.14 −0.05 0.00 −0.08 [0.06] [0.05] [0.10] [0.07] [0.06] [0.09] [0.07] [0.06] [0.09] [0.06] [0.05] [0.07]
ez m 0.00 0.05** −0.02 0.04 0.04 0.06 −0.02 0.05** −0.03 0.03 0.06*** 0.05 [0.02] [0.02] [0.03] [0.03] [0.02] [0.04] [0.03] [0.03] [0.04] [0.02] [0.02] [0.03]
ez indpro 0.03** 0.03*** 0.02* 0.05*** 0.02* 0.05*** 0.02 0.03*** 0.01 0.04*** 0.04*** 0.05***
[0.01] [0.01] [0.01] [0.01] [0.01] [0.02] [0.01] [0.01] [0.02] [0.01] [0.01] [0.02] crisis −0.44* 0.29* −0.56 −0.49* −0.05 −0.28 −0.69** 0.14 −0.73 −0.29 0.13 −0.29
[0.24] [0.17] [0.53] [0.26] [0.18] [0.52] [0.30] [0.21] [0.49] [0.24] [0.14] [0.34] cons −0.44** −0.57*** −0.41 0.22 −0.09 0.15 −0.20 −0.20 −0.23 −0.29 −0.41*** −0.26
[0.20] [0.18] [0.37] [0.24] [0.21] [0.39] [0.26] [0.24] [0.54] [0.19] [0.15] [0.24]
N 168 168 166 168 168 166 167 167 166 167 167 166 R2 0.22 0.16 0.22 0.15 0.09 0.14 0.17 0.06 0.17 0.21 0.19 0.21
dcc us fsi pgdp 1 dcc us fsi pgdp 2 dcc us fsi pgdp 3 dcc us fsi pgdp 4
OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS
us fsi 0.32*** 0.31*** 0.16*** 0.14 0.28*** 0.32*** 0.24*** 0.27**
[0.05] [0.10] [0.05] [0.10] [0.05] [0.11] [0.06] [0.12] us pgdp 0.07 0.06 0.14** 0.14 0.19*** 0.21 0.03 0.06
[0.09] [0.17] [0.06] [0.12] [0.07] [0.14] [0.06] [0.08] us cbrate 0.15*** 0.16*** 0.16*** 0.06** 0.06** 0.07 0.05 0.06* 0.05 0.12*** 0.13*** 0.12**
[0.03] [0.03] [0.06] [0.02] [0.02] [0.05] [0.03] [0.03] [0.06] [0.02] [0.02] [0.05] us m 0.03** 0.04*** 0.02 0.05*** 0.05*** 0.05*** 0.07*** 0.07*** 0.07*** 0.04*** 0.05*** 0.05***
[0.01] [0.01] [0.02] [0.01] [0.01] [0.02] [0.01] [0.01] [0.01] [0.01] [0.01] [0.01] us indpro 0.04*** 0 0.03 0.04*** 0.02 0.04* 0.05*** 0.01 0.06*** 0.06*** 0.03*** 0.07***
[0.01] [0.01] [0.03] [0.01] [0.01] [0.02] [0.01] [0.01] [0.02] [0.01] [0.01] [0.02] crisis 0.48*** 0.65*** 0.53** 0.33** 0.32** 0.39* 0.36* 0.39** 0.39 0.32** 0.47*** 0.36
[0.15] [0.14] [0.25] [0.15] [0.12] [0.24] [0.19] [0.15] [0.30] [0.16] [0.13] [0.26] cons −1.24*** −1.14*** −1.24** −1.26*** −0.92*** −1.32*** −1.20*** −0.77*** −1.30*** −1.19*** −1.17*** −1.30***
[0.29] [0.12] [0.52] [0.20] [0.10] [0.38] [0.24] [0.13] [0.45] [0.20] [0.10] [0.34]
N 229 229 227 229 229 227 229 229 227 229 229 227 R2 0.24 0.15 0.24 0.17 0.13 0.17 0.32 0.24 0.32 0.3 0.24 0.3
dcc ez fsi pgdp 1 dcc ez fsi pgdp 2 dcc ez fsi pgdp 3 dcc ez fsi pgdp 4
OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS
ez fsi 0.28 0.35 0.01 0.55 −1.07 −0.78 1.19*** 1.57*** [0.63] [0.85] [0.51] [1.18] [0.65] [1.58] [0.43] [0.42]
ez pgdp 0.03 0.08 0 0 0.37* 0.36 0.23** 0.21**
[0.12] [0.19] [0.15] [0.23] [0.21] [0.51] [0.11] [0.09] ez cbrate −0.22*** −0.20*** −0.20*** 0.16*** 0.16*** 0.12 0.08 0.03 0.08 −0.07 −0.01 −0.09**
[0.05] [0.05] [0.06] [0.06] [0.05] [0.09] [0.08] [0.07] [0.15] [0.04] [0.04] [0.04] ez m 0.00 0.01 −0.01 0.00 0.00 −0.01 0.00 0.01 −0.01 −0.04** 0.00 −0.04**
[0.02] [0.02] [0.03] [0.03] [0.02] [0.05] [0.03] [0.03] [0.07] [0.02] [0.02] [0.02] ez indpro 0.02* 0.02* 0.02* 0.01 0.01 0.01 0.02** 0.03*** 0.02 0.01 0.00 0.01**
[0.01] [0.01] [0.01] [0.01] [0.01] [0.01] [0.01] [0.01] [0.02] [0.01] [0.01] [0.01]
86 C. Blot et al. / Journal of Financial Stability 16 (2015) 71–88
Table 6 (Continued)
dcc ez fsi pgdp 1 dcc ez fsi pgdp 2 dcc ez fsi pgdp 3 dcc ez fsi pgdp 4
OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS OLS OLS 2SLS
crisis −0.49* −0.40** −0.52 0.04 0.04 −0.21 0.75* 0.13 0.57 −0.61*** −0.23* −0.76*** [0.29] [0.15] [0.45] [0.29] [0.14] [0.56] [0.40] [0.23] [0.69] [0.20] [0.12] [0.21]
cons 0.94*** 0.95*** 0.89** −0.57* −0.56*** −0.44 −1.00** −0.32 −0.88 −0.06 0.10 0.00 [0.24] [0.18] [0.37] [0.29] [0.17] [0.33] [0.42] [0.26] [0.75] [0.20] [0.14] [0.14]
N 168 168 166 168 168 166 167 167 166 167 167 166 R2 0.14 0.14 0.14 0.12 0.12 0.12 0.08 0.04 0.08 0.12 0.04 0.12
Robust standard errors in brackets using heteroskedastic and autocorrelation-consistent (HAC) robust variance estimates in order to mitigate potential generated dependent variable biases. The dependent variables are the dynamics conditional correlations (DCC) estimated in the previous section for the US and the EZ, for both the link between FSI and CPI or PGDP, using the 4 different models described in the related section. For each time series of correlation, we estimate the coefficients of (i) its potential determinants using OLS, (ii) removing FSI and CPI or PGDP that co-move with the dependent variable using OLS, and (iii) using IV-2SLS using the first two lags of FSI and CPI or PGDP and the first lag of the other independent variables as instruments. The p-value of the Hansen J statistic testing for the overidentification of all instruments suggest in all cases that the set of instruments is valid (uncorrelated with the error term). The p-value of the Kleibergen-Paap LM statistic testing for underidentification of all instruments is c nd co
h o d u t b a r fi c w b t A a o m A w
4
w a t a o c b S a s p a t t r i s
5 s
r
b a c p c o 2 d
u i a t m t a w t t t 1 W e t
i h fi h o b t h n r g between price and financial indices is stronger. It seems therefore that, for the United States, there is some truth in the argument outlined above (Sections 2.2 and 2.3) that over-borrowing may be
9 By construction, the DCC estimates are confined within the interval
omprised between 0.01 and 0.20 and suggests that the instrument set is relevant a * p < 0.10
** p < 0.05 *** p < 0.01.
ard to conclude that ensuring price stability can be a necessary r sufficient condition to achieving financial stability. Even more isturbing for the conventional wisdom is the fact that, when one ses models that include the US GDP deflator, the dynamic correla- ion is clearly negative over some periods. This is notably the case etween the early 2000s and mid-2007. It is even more striking fter 2003 when the DCC exhibits a clear and long-lasting negative elationship. This negative correlation appears in all the four speci- cations. During this sub-period of great moderation, inflation was ontained and financial imbalances, notably in the housing market ere growing. This result lends support to the paradox of credi-
ility illustrated by Borio and White (2004) and White (2006) and o the change in risk perception or risk tolerance highlighted by drian and Shin (2009) and Rajan (2005). At a low inflation rate nd low interest rate, the search for high yields and the expansion f banks’ balance sheets lead to the rise of a risk-taking channel of onetary policy. Empirical evidence in this sense can be found in ltunbas et al. (2014) for 1100 banks from 15 countries. Section 5 ill provide further insights into this issue.
.4. Robustness with stock prices
For robustness purposes, we perform the same three exercises hile replacing the FSI with stock market prices. Stock markets are
lready included in the FSI. The robustness analyses may then help o assess whether the results hold with an observable variable and
narrower definition of financial stability that would boil down to ne peculiar asset price. Table 5 presents the results for the simple orrelation coefficients. For the US, the results remain the same ut in the Eurozone they are now clearly negative and significant. catterplots are shown in Fig. 5. IRFs from the VAR methodology re represented in Fig. 6. Inflation shocks still negatively affect the tock markets in the US and in the Eurozone, while shocks to stock rices have no significant effect on inflation. Finally, DCC results re presented in Fig. 7: in accordance with former DCC outcomes, hey change sign several times over the period as a whole, showing hat the stock prices-price stability nexus evolves over time. All obustness tests thus confirm the earlier results: empirically, there s no support for the conventional wisdom, neither in the Eurozone ince 1999 nor in the US since 1993.
. Determinants of the link between price and financial
tability
As the final step in our analysis, we investigate whether the cor- elation between price and financial stability is explained by certain
[ l t v a
rrelated with endogenous regressors.
usiness cycle variables (the industrial production growth rate and financial crisis dummy) and/or monetary policy variables (the entral bank interest rate and the money aggregate growth rate), lus the FSI and the CPI separately. Finding determinants for this orrelation might possibly shed light on the time-varying nature f DCC estimates. To this end, we compute different OLS and IV- SLS estimations, using the DCC estimates from the four models escribed in Section 4.3 as the dependent variable.9
Because some of the independent variables co-move with, and nderlie, the dependent variable, there may be an endogeneity
ssue. For both the US and the EZ, for each link between the FSI nd CPI (or PGDP), and for each of the four models used, we herefore estimate three regressions: (i) including our 6 above-
entioned variables and using OLS, (ii) using OLS but removing he FSI and CPI (or PGDP) that co-move with the dependent vari- ble, and (iii) including again all 6 variables and using IV-2SLS ith the first two lags of FSI and CPI (or PGDP) and the first lag of
he other independent variables as instruments. Moreover, given hat the dependent variable is itself estimated in a previous step, his may cause underestimated standard errors (see Saxonhouse, 976, for more details on the estimated dependent variable bias). e therefore apply the Huber-White sandwich estimator for het-
roskedastic and autocorrelation-consistent (HAC) standard errors o mitigate this issue. The results are reported in Table 6.
In the US, several results can be identified. A higher financial nstability (superior to its mean) is positively correlated with a igher (superior to its mean) DCC correlation between price and nancial stability. The same result holds between, on the one and, higher money supply and higher industrial production and, n the other hand, a higher DCC correlation, and to a lesser extent, etween higher inflation and a higher DCC correlation. Turning to he Fed’s interest rate, it appears that the conventional instrument as no clear-cut impact on the DCC correlation. Overall, the busi- ess cycle and the money supply emerge as the main drivers of the elationship between price and financial stability. When money rowth is high, and the economy is booming, the correlation
−1; 1]. Antonakakis (2012) suggests applying a Fisher transformation, og((1 + �ij,t )/(1 − �ij,t )), to ensure that the dependent variable is not restricted o that interval. In this paper, we only provide the results with the non-transformed ariables, since the results are similar with the transformed variables. Estimates re available from the authors upon request.
ancial
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6
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S
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ne of the major channels through which inflation and financial nstability are linked (via the booming economy and/or exces- ive liquidity provision). This result supports the argument of runnermeier and Sannikov (2014) in favor of better coordinating onetary policy with financial stability policy: a higher liquidity
osition during downturns may well help curtail the balance sheet onstraints of banks at the expense of productive balance sheet- mpaired sectors, hence generating greater financial instability.
For the Eurozone, the results are less clear-cut. Contrary to he US case, the financial stability index and money supply have o effect on the DCC correlation between price and financial sta- ility; this is not really surprising, as EZ monetary authorities, specially before the current crisis, have been much more conser- ative than their Northern American counterparts in using liquidity njections as a policy tool. As in the US, central bank rates have a imited impact on the correlation: the ECB main refinancing oper- tion (MRO) rate has no explanatory power on the DCC correlation etween price and financial stability. The main result common to he US and the EZ is the positive effect of industrial production on he DCC correlation, suggesting that the link between price and nancial stability may be associated with the business cycle.
It is interesting to notice, in conclusion, that the central bank nterest rate plays no role in explaining changes in the DCC corre- ation between price and financial stability in either the US or the urozone. This, together with our main result that the correlation tself changes sign over time, casts doubts on the “leaning against he wind” strategy. As is clear from Woodford (2012), this strategy orks only if the relationship is stable and positive, and if the inter-
st rate instrument is effective in managing commodity and asset rices at the same time.
. Conclusion
This paper describes the relationship between price and finan- ial stability in the US and the Eurozone. The results are based on hree methodologies: simple correlation coefficient, VAR and DCC- ARCH. Finally, we examine the determinants that are correlated ith the DCC analysis. The main result is that no evidence sup- orts the conventional wisdom in the US or Eurozone economies ince the 1990s. None of the three empirical methodologies shows
robust positive link between financial and price stability and the ime-varying approach indicates that the relationship is undoubt- dly unstable.
This result suggests that the conventional wisdom is not empir- cally well grounded, at least over the period considered in the aper; this calls into question the relevance of policy prescriptions rawing from this “wisdom”. Evidence showed that financial insta- ility can develop even in a low inflation environment, as was the ase during the Great Moderation. Price stability has not been a ufficient condition to promote financial stability. Consequently, nancial stability should certainly be addressed independently of he objective of price stability. Some other results of this paper give rounds for a critical assessment of the “leaning against the wind” onetary policy in the Eurozone and the US. We show that the
entral bank interest rate has no effect on the computed correla- ion between financial and price stability. In contrast, variations n monetary aggregates have a significant impact on the com- uted correlation between financial and price stability, which lends upport to the requirement of a better coordination of monetary olicy and financial stability policy. Consequently, financial stabil-
ty should be addressed with instruments other than simply the
nterest rate fixed by central banks. Macro and micro regulations
ay prove useful to fostering financial stability. It is worth noticing, in conclusion, that the present empiri-
al exercise focuses on a specific period when inflation has been
A
A
Stability 16 (2015) 71–88 87
oderate, and there may be other periods or other monetary egimes when the conventional wisdom might have been more rel- vant. The analysis of the determinants of the link between price nd financial stability suggests that the correlation increases with oney supply growth, and this may call for analyzing the stability
f the price and financial stability relation across different mone- ary regimes over very long periods of time. This issue is left for urther research.
ppendix A.
See Table A.1.
able A.1 TLFSI and CISS constituents.
STLFSI Interest Rates
• Effective federal funds rate • 2-year Treasury • 10-year Treasury • 30-year Treasury • Baa-rated corporate • Merrill Lynch High-Yield Corporate Master II Index • Merrill Lynch Asset-Backed Master BBB-rated
Yield Spreads
• Yield curve: 10-year Treasury minus 3-month Treasury • Corporate Baa-rated bond minus 10-year Treasury • Merrill Lynch High-Yield Corporate Master II Index minus 10-year Treasury • 3-month London Interbank Offering Rate–Overnight Index Swap (LIBOR-OIS) spread • 3-month Treasury-Eurodollar (TED) spread 3-month commercial paper minus 3-month Treasury bill
Other Indicators
• J.P. Morgan Emerging Markets Bond Index Plus • Chicago Board Options Exchange Market Volatility Index (VIX) • Merrill Lynch Bond Market Volatility Index (1-month) • 10-year nominal Treasury yield minus 10-year Treasury
CISS Money market
• Realized volatility of the 3-month Euribor rate • Interest rate spread between 3-month Euribor and 3-month French T bills • Monetary Financial Institution’s (MFI) emergency lending at Eurosystem central banks: MFI’s recourse to the marginal lending facility, divided by their total reserve requirements
Bond market
• Realized volatility of the German 10-year benchmark government bond index • Yield spread between A-rated non-financial corporations and government bonds (7-year maturity bracket) • 10-year interest rate swap spread
Equity market
• Realized volatility of the Datastream non-financial sector stock market index • CMAX for the Datastream non-financial sector stock market index • Stock-bond correlation
Financial interme- diaries
• Realized volatility of the idiosyncratic equity return of the Datastream bank sector stock market index over the total market index • Realized volatility calculated as the weekly average of absolute daily idiosyncratic returns • Yield spread between A-rated financial and non-financial corporations (7-year maturity) • CMAX as interacted with the inverse price-book ratio (book-price ratio) for the financial sector equity market index
Foreign exchange market
Realized volatility of the euro exchange rate vis-à-vis the US dollar, the Japanese Yen and the British Pound
ource: Hollo et al. (2012) and Federal Reserve Bank of St Louis (2010).
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- Assessing the link between price and financial stability
- 1 Introduction
- 2 Related literature
- 2.1 The conventional wisdom
- 2.2 Theoretical linkages between price and financial stability
- 2.3 Implications in terms of policy strategies
- 3 Data
- 4 Identifying the link between price and financial stability
- 4.1 Simple correlation
- 4.2 VAR
- 4.3 Dynamic conditional correlations
- 4.4 Robustness with stock prices
- 5 Determinants of the link between price and financial stability
- 6 Conclusion
- References
- References
Defining Financial Stability.pdf
WP/04/187
Defining Financial Stability
Garry J. Schinasi
© 2004 International Monetary Fund WP/04/187
IMF Working Paper
International Capital Markets Department
Defining Financial Stability1
Prepared by Garry J. Schinasi
October 2004
Abstract
This Working Paper should not be reported as representing the views of the IMF. The views expressed in this Working Paper are those of the author(s) and do not necessarily represent those of the IMF or IMF policy. Working Papers describe research in progress by the author(s) and are published to elicit comments and to further debate.
The main objective of this paper is to propose a definition of financial stability that has some practical and operational relevance. Financial stability is defined in terms of its ability to facilitate and enhance economic processes, manage risks, and absorb shocks. Moreover, financial stability is considered a continuum: changeable over time and consistent with multiple combinations of the constituent elements of finance. The paper also discusses several practical implications of the definition that should be considered when using it for policy analysis or developing an analytical framework. JEL Classification Numbers: E60, G00, H00 Keywords: Finance, stability, fragility, crises Author(s) E-Mail Address: [email protected]
1 This paper was written while on sabbatical from the IMF and is part of a manuscript on financial stability issues. I gratefully acknowledge the IMF’s financial support under its Independent Study Leave Program. I also gratefully acknowledge the support and encouragement of De Nederlandsche Bank (DNB) and the European Central Bank (ECB) while visiting them in 2003 and 2004, especially Tommaso Padoa-Schioppa, Mauro Grande, and John Fell at the ECB and Henk Brouwer, Jan Brockmeijer, Aerdt Houben, and Jan Kakes at the DNB. I am grateful to Tommaso Padoa-Schioppa, John Fell, Mauro Grande, Aerdt Houben, Jan Kakes, and Jukka Vesala for extensive discussions on this topic and for comments on earlier drafts of this paper.
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Table of Contents
Page
I. Introduction....................................................................................................................3
II. Prior Concepts of Finance and Finance’s Strengths and Weaknesses ...........................4
III. Key Principles for Defining Financial Stability.............................................................6
IV. Definition of Financial System Stability........................................................................8
V. Some Practical Implications of the Definition.............................................................11
Annex: Alternative Definitions of Financial Stability .............................................................13 References................................................................................................................................17
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I. INTRODUCTION
Does financial stability require the soundness of institutions, the stability of markets, the absence of turbulence, low volatility, or something more fundamental? Can it be achieved and maintained through individual private actions and unfettered market forces alone? If not, what is the role of the public sector in fostering financial stability, as opposed to private- collective action: is it just to make way for the private sector to achieve an optimum on its own, or is a more proactive role necessary for achieving the full private and social benefits of finance? Is there a consensus on how to achieve and maintain financial stability?
The last three questions are not likely to have clear answers without a useful answer to the first question. Likewise, without a good working definition, the growing financial stability profession will continue to find it difficult to develop useful analytical frameworks for examining policy issues. Unfortunately, there is no single, widely accepted and used definition of financial stability. There have been recent attempts to define financial stability, but most of them seem to fit into a particular theme of a paper or speech. In addition, most authors prefer to define financial instability or systemic risk (see the attached Annex starting on page 13).
The approach taken here is to define financial stability rather than its absence, in part because this is likely to be the more useful “policy” objective. A policy objective of avoiding financial instability or crisis—or of managing systemic risk—could bias policy decisions, analyses, and analytical frameworks towards sacrificing both private and social benefits of finance. A more positive or constructive approach—such as the one proposed in this paper— may serve additional practical purposes, including leaving open the possibility of assessing whether the private and social benefits of finance can be increased further. This would be particularly useful in countries that have relatively undeveloped financial systems.
As anyone who has tried to define financial stability knows, there is as yet no widely accepted model or analytical framework for assessing financial system stability and for examining policies as there is for economic systems and in other disciplines.2 This is because the analysis of financial stability is still in its infant stage of development and practice, as compared with—for example—the analysis of monetary and/or macroeconomic stability. In the rare cases in which financial systems are expressed rigorously, they constitute one or two equations in a much larger macroeconomic model possessing most of the usual macro- equilibrium and macro-stability conditions. In addition, there are reasons to believe that a single target variable cannot be found for defining and achieving financial stability—as there is believed to be for defining and achieving monetary stability—although many doubt that a single target variable approach accurately represents actual practice in monetary policymaking.
2 See the paper by Houben, Kakes, and Schinasi (2004), which proposes a framework for financial stability (and also draws on concepts developed here). The IMF’s bilateral and multilateral financial market and system surveillance, and the IMF’s and World Bank’s Financial Sector Assessment Program are also making progress in this direction.
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Lacking a framework, a set of models, or even a concept of equilibrium, it is difficult to envision a definition of financial stability akin to that which economists normally demand and use. Nevertheless, it would be useful to have one that allows for the development of policy frameworks and analytical tools. The definition proposed in this paper is one step in this direction, and is offered for wider debate.
The paper is organized as follows: Section II briefly presents some prior concepts of finance and its strengths (benefits) and weaknesses (fragilities), drawing on analysis in a companion study. These concepts serve as both practical and analytical focal points for developing a concept of financial stability in the absence of a widely accepted concept of equilibrium and analytical framework. For simplicity, Section III identifies five principles that a useful definition could encompass. It also makes a case for seeing financial stability as occurring along a changeable continuum or range of conditions of the constituent parts of the financial system, as opposed to a single configuration or state of these parts as is most often used in microeconomic and macroeconomic models. Section IV proposes a broad definition and discusses the meaning of some of its language. The final section identifies several practical implications of the definition that should be carried over into any policy or analytical framework that utilizes it.
II. PRIOR CONCEPTS OF FINANCE AND FINANCE’S STRENGTHS AND WEAKNESSES
Before developing a working definition of financial stability, it would be useful to consider the following understandings as prerequisites or as relevant concepts and ideas.3
First, a barter economy is less effective and efficient in allocating scarce resources than is an economy with the ability to use financial claims on future real resources. A discussion of financial stability must necessarily take place within the context of a monetary economy in which there exists a money (now usually fiat money) that is universally accepted as the economy’s unit of account and means of payment.
Second, money is not necessarily the most desirable store of value—except in the very short run or during episodes of financial distress and dysfunctions. Throughout recorded history, human ingenuity has driven an evolutionary process of finance to overcome this persistent deficiency. Modern finance provides substitutes for money that provide temporary and reversible intertemporal means-of-payment and store-of-value services. These substitutes are promises to pay money in the future and are designed in part to facilitate intertemporal resource allocations.
Third, many of the services provided by money and finance are both private and public goods. They are private goods in providing benefits to individuals in their private affairs, benefits that convey only to the counterparts engaged in specific transactions. They separately and jointly provide public goods as well, because they allow multilateral trade and exchange to be more efficient, in part by eliminating the need for Jevons’ “double coincidence of wants,” both sectorally at moments in time and intertemporally. In addition, 3 See Schinasi (2004) for a more detailed discussion and analysis of many of these points.
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finance provides public goods beyond those of fiat money: by enhancing and distributing the public-good characteristics of fiat money, finance enlarges society’s opportunities for—and efficiency in—intertemporal economic processes such as trade, production, wealth accumulation, economic development and growth, and ultimately social prosperity. In sum, the universal acceptability of money and the existence of an effective process of finance together create an environment that provides collective benefits to all members of society.
Fourth, an alternative and useful way of seeing finance is to bring to the surface one of its defining characteristics. Unlike fiat money—which eliminates the element of human trust in trade and exchange—finance involves human promises to pay back specific amounts of fiat money in the future. In this way, finance existentially embodies uncertainty (about human trust). Modern financial systems have evolved to provide beneficial and necessarily imperfect ways of transforming this fundamental uncertainty into quantifiable and “priceable” risks, such as default risk, and, through social arrangements (both markets and financial institutions), also market risk, liquidity risk, and so on. In less traditional but no less appropriate terms, modern finance provides societies with effective, albeit imperfect, mechanisms for transforming, pricing, and allocating economic and financial uncertainties and risks.
Finally, because finance existentially embodies uncertainty, there are both potential benefits and costs associated with it.4 On the one hand, finance enhances the private and social benefits of fiat money: in part by enlarging the pool of liquidity available for production, consumption, and exchange; and in part by facilitating and enhancing the efficiency of intertemporal economic processes. In effect, the willingness to engage in finance (i.e., to take the leap of faith) and accept the uncertainty of trust has created social welfare gains far beyond what fiat money alone could provide.
On the other hand, trust is fragile: it can, and often enough does, become a source of potential financial instability, which in the wrong circumstances can affect both individual and social welfare. To the extent that doubts about human trust are transformed by the financial system into market and other financial risks, they too can become companion sources of instability—even more so if a society’s financial-market mechanisms are impaired and unable to effectively reallocate and price such doubts. How such doubts propagate through the financial system is an important determinant of whether they either self-correct and remain isolated and harmless or become widespread, harmful, and perhaps even systemic. Because finance supports and facilitates real economic processes, these potential instabilities may well extend to the real economy.
4 Diamond and Dybvig (1983) and Diamond and Rajan (2000) explore this in the context of bank intermediation.
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III. KEY PRINCIPLES FOR DEFINING FINANCIAL STABILITY
While there is scope for being more comprehensive and inclusive, a small number of key principles can be identified for developing a working definition of financial stability.5 One that requires more elaboration than the others is that it is useful to consider financial stability as occurring along a continuum—rather than as a static condition.
The first principle is that financial stability is a broad concept, encompassing the different aspects of finance (and the financial system)—infrastructure, institutions, and markets. Both private and public persons participate in markets and in vital components of the financial infrastructure (including the legal system and official frameworks for financial regulation, supervision, and surveillance). Governments borrow in markets, hedge risks, operate through markets to conduct monetary policy and maintain monetary stability, and own and operate payments and settlement systems. Accordingly, the term “financial system” can be seen as encompassing both the monetary system with its official understandings, agreements, conventions, and institutions as well as the processes, institutions, and conventions of private financial activities.6 Given the tight interlinkages between all of these components of the financial system, (expectations of) disturbances in any of the individual components can undermine the overall stability, requiring a systemic perspective. At any given time, stability or instability could be the result of either private institutions and actions, or official institutions and actions, or both simultaneously and/or iteratively.
A second useful principle is that financial stability not only implies that finance adequately fulfills its role in allocating resources and risks, mobilizing savings, and facilitating wealth accumulation, development, and growth; it should also imply that the systems of payment throughout the economy function smoothly (across official and private, retail and wholesale, and formal and informal payments mechanisms). This requires that fiat (or central bank) money—and its close-substitute, derivative monies (such as demand deposits and other bank accounts)—can adequately fulfill its role as the universally accepted means of payment and unit of account and, when appropriate, as a (short-term) store of value. In other words, financial stability and what is usually regarded as a vital part of monetary stability overlap to a large extent.
A third principle is that the concept of financial stability relates not only to the absence of actual financial crises but also to the ability of the financial system to limit, contain, and deal with the emergence of imbalances before they constitute a threat to itself or economic processes. In a well-functioning and stable financial system, this occurs in part through self-corrective, market-disciplining mechanisms that create resilience and prevent
5 There are also many prerequisites for establishing a sound and stable financial system, such as: macroeconomic stability and a policy framework for maintaining it; an adequate—if not effective—framework for financial regulation, supervision, and surveillance (implicitly mentioned in the text as infrastructure; well- established codes, standards, and business practices), and more generally private incentive structures; and an enforceable legal system that supports productive private financial contracts.
6 This is adapted from the definition of “international financial system” in Truman (2003).
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problems from festering and growing into system-wide risks. In this respect, there may be a policy-related trade-off entailing the choice between allowing market mechanisms to work to resolve potential difficulties and intervening quickly and effectively—through liquidity injections via markets, for example—to restore risk-taking and/or to restore stability. Thus, financial stability entails both preventive and remedial dimensions.
A fourth important principle is that financial stability be couched in terms of the potential consequences for the real economy. Disturbances in financial markets or at individual financial institutions need not be considered threats to financial stability if they are not expected to damage economic activity at large. In fact, the incidental closing of a financial institution, a rise in asset-price volatility, and sharp and even turbulent corrections in financial markets may be the result of competitive forces, the efficient incorporation of new information, and the economic system’s self-correcting and self-disciplining mechanisms. By implication, in the absence of contagion and the high likelihood of systemic effects, such developments may be viewed as welcome—if not healthy—from a financial stability perspective.
A fifth principle—consistent with those already discussed and the actual dynamism of finance—is that financial stability be thought of as occurring along a continuum. An example that is more transparent is the health of an organism, which also occurs along a continuum. A healthy organism can usually reach for a greater level of health and well being, and the range of what is normal is broad and multi-dimensional. In addition, not all states of un- health (or illness) are significant, systemic, or life threatening. And some illnesses, even temporarily serious ones, allow the organism to continue to function productively and can have a cleansing effect, leading to greater health. One implication of seeing financial stability in this way is that maintaining financial stability does not necessarily require that each part of the financial system operate persistently at peak performance; it is consistent with the financial system operating on a “spare tire” from time to time.7
The concept of a continuum is relevant because finance fundamentally involves uncertainty, is dynamic (meaning both inter-temporal and innovative), and is composed of many interlinked and evolutionary elements (infrastructure, institutions, markets). Accordingly, financial stability is expectations-based, dynamic, and dependent on many parts of the system working reasonably well. What might represent stability at one point in time, might be more stable or less stable at some other time, depending on other aspects of the economic system—such as technological, political, and social developments. Moreover, financial stability can been seen as being consistent with various combinations of the conditions of its constituent parts, such as the soundness of financial institutions, financial markets conditions, and effectiveness of the various components of the financial infrastructure.
7 See Greenspan (1999).
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IV. DEFINITION OF FINANCIAL SYSTEM STABILITY
Broadly, financial stability can be thought of in terms of the financial system’s ability: (a) to facilitate both an efficient allocation of economic resources—both spatially and especially intertemporally—and the effectiveness of other economic processes (such as wealth accumulation, economic growth, and ultimately social prosperity); (b) to assess, price, allocate, and manage financial risks; and (c) to maintain its ability to perform these key functions—even when affected by external shocks or by a build up of imbalances—primarily through self-corrective mechanisms.
A definition consistent with this broad view is as follows:
A financial system is in a range of stability whenever it is capable of facilitating (rather than impeding) the performance of an economy, and of dissipating financial imbalances that arise endogenously or as a result of significant adverse and unanticipated events.
The meanings of several phrases need to be explained.
First, the concept of a range of stability represents the concept of a continuum as a key building block. The continuum for financial stability can be thought of as multidimensional and occurring across a multitude of observable and measurable variables. The set of variables should encompass a subset that tries to quantify, albeit imperfectly, how well finance is facilitating economic and financial processes such as savings and investment, lending and borrowing, liquidity creation and distribution, asset pricing, and ultimately wealth accumulation and growth.
As a continuum, financial stability can be seen practically as somewhat broader and less precise than the ability to return to a single and sustainable position or time path after a shock or perturbation, as with other (Newtonian) concepts of equilibrium and stability in some disciplines (including economics). The proposed definition is consistent with a financial system being in a perpetual state of flux and transformation while its ability to perform its key functions remains well within a set of tolerable boundaries—defined over a set of measurable variables—that are consistent with it successfully playing its important facilitative and efficiency-enhancing roles. Observable states approaching these boundaries would indicate that the financial system is losing some of its ability to perform; observations outside these boundaries would indicate that the system is no longer effectively facilitating economic processes, perhaps because aggregate production is substantially below its potential on account of funds not being channeled to profitable activities, risks not being managed, and shocks not being absorbed. In such cases, remedial action would be required, which in the extreme would mean crisis resolution and restoration.
To illustrate the multidimensional nature of the definition, consider a very simplistic two-dimensional example. In assessing the joint stability of financial markets and financial institutions, one might be able to identify combinations of interest rate spread volatility (as a possible market source of instability) and banking system capital (as an institutional source of shock-absorptive capacity) that are consistent with the financial system continuing
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effectively to facilitate efficient resource allocation. Likewise, other combinations could be identified that would not be consistent with stability. The former would constitute the range of stability and the latter would fall outside this range.
A more comprehensive sets of factors could be envisioned for determining a grid over which a continuum is defined. Statistical tools could be utilized to select such factors by considering historical episodes of both stability and instability, in part by using forward- looking, market-determined expectations of future outcomes and matching them with actual outcomes. This methodology could, in principle, also help to establish estimates of boundaries or zones separating stability from potential instability.8
A second phrase that needs some explanation is facilitating (rather than impeding) the performance of an economy. This phrase means, among other things, that finance is contributing to (rather than impeding) the efficient allocation of real resources, the rate of growth of output, and the processes of saving, investment, and wealth creation—and may also entail and include other observable and measurable aspects of economic performance.
Third, the term, “dissipate financial imbalances,” means a movement along the continuum in the direction of stability (away from boundaries) and not instability, for example in asset prices and portfolio flows, implicitly through self-corrective mechanisms. Such adjustments would include the exit and entry of market participants (financial institutions or nonfinancial entities acting on behalf of others or individuals acting directly in the markets).
There are other aspects of the definition worth noting. The proposed definition leaves open the possibility that the financial system could become capable of impeding the performance of the economy endogenously, even in the absence of unanticipated events (shocks), for example through the accumulation of imbalances caused by asset mispricing and/or other market “imperfections.” This is consistent with the ample historical evidence that financial systems, particularly banking systems, are prone to the build up of imbalances (credit-risk concentrations or illiquidity, for example) and even instability. Banks internalize the fragilities associated with the properties of liquidity, and are therefore prone to instability themselves.9 Banks, other financial institutions, and even markets can be seen as social arrangements—or as clearing houses—for assessing, pricing, and trading human promises necessarily involving uncertainty and risk, including uncertainty about the fundamental element of trust in financial contracts. Social arrangements and institutional features of economic systems try to internalize the potential adverse consequences of negative externalities associated with the frailties of human trust. A tangible example of this is that banks internalize the potential adverse consequences of failures of trust by economizing on
8 In principle, this approach could be generalized and made amenable to theoretical and empirical model building. For example, one could define a set of n variables that encompass all relevant measures of aspects of financial stability. The range of stability could be defined as a subset of n-tuples bounded by n functions (most likely nonlinear) defining the limits of stability in terms of n variables.
9 See Diamond and Rajan (2000 and 2002).
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information about large pools of debtors and their ability to pay future claims or promissory notes. In internalizing these elements of financial risk and uncertainty, financial institutions and markets themselves embody the potential for financial fragility, which ultimately finds its source in a failure of human trust in some meaningful way (for example, a default).
The definition also presupposes that there are aspects of finance that embody either negative or positive externalities. In this sense, improvements in the ability of finance to facilitate rather than impede economic processes—including providing greater financial stability—is welfare improving in terms of enhancing the efficiency of resource allocation (and pricing), especially inter-temporally.10 Some points along the continuum of financial stability are more welfare-improving (and efficiency-enhancing) than others, and some points along the continuum of instability are to be avoided, seemingly at all costs.11 Thus, in moving from a condition of stability to instability, the contribution of the financial system to aggregate economic welfare is being reduced.
A stable financial system is one that enhances economic performance in many dimensions, whereas an unstable financial system is one that detracts from economic performance. In this sense the definition is “normative.” Ultimately—and unlike physical instabilities such as earthquakes, floods, and sunspots—financial instability can be dealt with through massive intervention by authorities, including redefining the rules of the market place. But these measures would be “last resort” reforms to prevent the economic system from collapsing—as, for example, during the world-wide depression in the 1930s and more recently in Asia during 1997–98.
To illustrate the broad nature of this definition of financial stability, two corollary definitions are useful:
(i) A financial system is entering a range of instability whenever it is threatening to impede the performance of an economy.
(ii) A financial system is in a range of instability when it is impeding performance and threatening to continue to do so.
A more general definition that does not require the specification of what constitutes a “financial system” is:
Financial stability is a condition in which an economy’s mechanisms for pricing, allocating, and managing financial risks (credit, liquidity, counterparty, market, etc.) are functioning well enough to contribute to the performance of the economy (as defined above).
10 See Schinasi (2004).
11 There would seem to be a trade-off in financial systems between financial stability and efficiency, but this is difficult to analyze given that there are different concepts of both stability and efficiency. There is some work on this in the theoretical banking literature, but none could be found at the financial-system level.
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V. SOME PRACTICAL IMPLICATIONS OF THE DEFINITION
Looking at financial stability in this way allows for the delineation of financial conditions and potential difficulties according to their intensity, scope, and potential threat to systemic stability. One could, for example, think of potential financial difficulties as falling into one of the following fairly broad categories:
• difficulties in a single institution or market not likely to have system-wide consequences for either the banking or financial system;
• difficulties that involve several relatively important institutions involved in market activities with some nontrivial probability of spillovers and contagion to other institutions and markets; and
• problems likely to spread to a significant number and types of financial institutions and across usually unrelated markets for managing liquidity needs, such as forward, interbank, and even equity markets.
Problems occurring within each of these categories would require different diagnostic tools and policy responses, ranging from doing nothing to intensifying supervision or surveillance of a specific institution or market, to liquidity injections into the markets to dissipate strains, to interventions into particular institutions.
The financial stability definition also involves several complexities that have practical significance in terms of assessing risks to the well-functioning of the financial system and the contribution public policy can make to ensuring financial stability.
• Developments in financial stability cannot be summarized in a single quantitative indicator. In contrast with price stability, for instance, there is as yet no unequivocal unit of measurement for financial stability.12 This reflects the multifaceted nature of financial stability as it relates to both the stability and resilience of financial institutions, and to the smooth functioning of financial markets and settlement systems. Moreover, diverse factors need to be weighed in terms of their potential ultimate influence on real economic activity.
• Developments in financial stability are inherently difficult to forecast. Assessing the state of financial stability should not only take stock of disturbances as they emerge, but also indicate the risks and vulnerabilities that could lead to such disturbances occurring in the future. A forward-looking approach is therefore needed in order to establish the build-up of risks and imbalances and to take account of the transmission lags in policy instruments. The challenge is that financial crises are inherently difficult to predict because of many factors, for example, contagion effects and nonlinearities in the relationships between the constituent parts of finance. In
12 See Andy Haldane (2004) for an attempt to set out how this might be done for financial stability.
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addition, risks to financial stability often reflect the far-reaching consequences of unlikely events. This implies that the focus of attention should not be the mean, median, or mode of possible outcomes or states but the entire distribution of them, and particularly the left “tail.” Beyond this, the distribution of possible outcomes may be subject to greater fundamental uncertainty (in the sense of Knight, 1921) than traditional macroeconomic projections, reflecting lack of knowledge about the actual shape of the probability distribution. This would imply that forecasts of financial stability might be inherently less reliable than forecasts of monetary or macroeconomic stability, for which there are well-worked and more reliable models and more timely and useful data. Thus, in the large sets of financial indicators that are now being used by central banks and international financial institutions, the relationships between indicators and financial stability conditions may not be strong or robust enough to be reliable for assessments and prediction. Nevertheless, in looking at a broader array of indicators, in developing better frameworks, and in utilizing sophisticated statistical tools, there may be scope for improving the ability to monitor and assess financial stability in the future.
• Developments in financial stability are only partly controllable. The policy instruments that can be used to safeguard financial stability generally have other primary objectives, such as protecting the interests of deposit holders (in the case of prudential instruments), fostering price stability (in the case of monetary policy), or promoting a swift settlement of financial transactions (in the case of policies governing payment and settlement systems). Besides timing lags, the impact of these policy instruments on financial stability is thus often indirect; in some cases there may even be friction with the instrument’s initial objective. Moreover, developments in financial stability are highly susceptible to exogenous shocks—ranging from natural catastrophes to abrupt swings in market sentiment—further limiting their controllability.
• Policies aimed at financial stability often involve a trade-off between resilience and efficiency. Measures to enhance financial stability often involve weighing the pursuit of an efficient allocation of financial resources against the ability to exclude or absorb shocks to the financial system. This implies a risk/return judgment that is difficult to make in a fully objective manner. For instance, in the sphere of prudential policies, higher solvency requirements will reduce the risk of a bank not being able to absorb an adverse shock but will also imply capital costs and foregone investment opportunities. Similarly, exchange restrictions may reduce or exclude certain risks related to international capital flows but may also limit the efficiency of the domestic financial market.
• Policy requirements for financial stability may be time inconsistent. Since the use of some public policy instruments to safeguard financial stability circumvents market forces, the short-term stability gain may come at the cost of a longer-term stability loss. In particular, measures such as the provision of lender-of-last-resort finance or deposit guarantee may undermine market discipline, thereby creating moral hazard or adverse selection. This intertemporal trade off is a fundamental issue in financial system policymaking.
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ALTERNATIVE DEFINITIONS OF FINANCIAL STABILITY
This appendix provides an overview of definitions or descriptions of financial stability by a selected group of officials, central banks, and academics.13
John Chant and others (Bank of Canada)14
“Financial instability refers to conditions in financial markets that harm, or threaten to harm, an economy’s performance through their impact on the working of the financial system.... Such instability harms the working of the economy in various ways. It can impair the financial condition of non-financial units such as households, enterprises, and governments to the degree that the flow of finance to them becomes restricted. It can also disrupt the operations of particular financial institutions and markets so that they are less able to continue financing the rest of the economy.... It differs from time to time and from place to place according to its initiating impulse, the parts of the financial system affected, and its consequences. Threats to financial stability have come from such diverse sources as the default on the bonds of a distant government; the insolvency of a small, specialized, foreign exchange bank; computer breakdown at a major bank; and the lending activities of a little- known bank in the U.S. Midwest (pp. 3–4).
Andrew Crockett (Bank for International Settlements and Financial Stability Forum)15
“...define financial stability as an absence of instability...a situation in which economic performance is potentially impaired by fluctuations in the price of financial assets or by an inability of financial institutions to meet their contractual obligations. I would like to focus on four aspects of this definition.
“Firstly, there should be real economic costs.... Secondly, it is the potential for damage rather than actual damage which matters.... Thirdly, my definition refers...not just to banks but to nonbanks, and to markets as well as to institutions.... Fourth, my definition allows me to address the question of whether banks are special...all institutions that have large exposures—all institutions that are largely interconnected whether or not they are themselves directly involved in the payments system—have the capacity, if they fail, to cause much widespread damage in the system.”
13 Some authors choose not to define financial stability and instead use the concept of systemic risk. See Oosterloo and Haan (2003) for a discussion of this concept.
14 See Chant (2003).
15 See Crockett (1997).
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Deutsche Bundesbank16
“The term financial stability broadly describes a steady state in which the financial system efficiently performs its key economic functions, such as allocating resources and spreading risk as well as settling payments, and is able to do so even in the event of shocks, stress situations, and periods of profound structural change.”
Wim Duisenberg (European Central Bank)17
“...monetary stability is defined as stability in the general level of prices, or as an absence of inflation or deflation. Financial stability does not have as easy or universally accepted a definition. Nevertheless, there seems to be a broad consensus that financial stability refers to the smooth functioning of the key elements that make up the financial system.”
Roger Ferguson (Board of Governors of the U.S. Federal Reserve System)18
“It seems useful...to define financial stability...by defining its opposite: financial instability. In my view, the most useful concept of financial instability for central banks and other authorities involves some notion of market failure or externalities that can potentially impinge on real economic activity.
“Thus, for the purposes of this paper, I’ll define financial instability as a situation characterized by these three basic criteria: (i) some important set of financial asset prices seem to have diverged sharply from fundamentals; and/or (ii) market functioning and credit availability, domestically and perhaps internationally, have been significantly distorted; with the result that (iii) aggregate spending deviates (or is likely to deviate) significantly, either above or below, from the economy’s ability to produce.
Michael Foot (U.K. Financial Services Authority)19
“...we have financial stability where there is: (a) monetary stability; (b) employment levels close to the economy’s natural rate; (c) confidence in the operation of the generality of key financial institutions and markets in the economy; and (d) where there are no relative price movements of either real or financial assets within the economy that will undermine (a) or (b).
“The first three elements of this definition are, I hope, noncontentious. In respect of (a) and (b), it seems implausible to define financial stability as occurring in a period of rapid inflation, or in a mid-1930s style period of low inflation but high unemployment.
16 Deutsche Bundesbank (2003).
17 See Duisenberg (2001).
18 See Ferguson (2003).
19 See Foot (2003).
- 15 - ANNEX
“Similarly in respect of (c), it would be strange to argue that there was financial stability in a period when banks were failing, or when normal conduits for long-term savings and borrowing in either the personal or corporate sectors were seriously malfunctioning. Such circumstances would mean the participants had lost confidence in financial intermediaries. It would mean, almost certainly, that economic growth was being damaged by the unavailability or relatively high cost of financial intermediation.
“This leaves us with (d).... I would say that there are four main channels by which changes in asset prices might affect the real economy: by changing household wealth and thereby consumption…by a change in equity prices...by their impact on firms’ balance sheets which can then affect corporate spending...[and] by their impact on capital flows, with for example inflows of capital—as during the dot.com boom in the US—strengthening the domestic currency.”
Sir Andrew Large20
“In a broad sense.....think of financial stability in terms of maintaining confidence in the financial system. Threats to that stability can come from shocks of one sort or another. These can spread through contagion, so that liquidity or the honoring of contracts becomes questioned. And symptoms of financial instability can include volatile and unpredictable changes in prices. Preventing this from happening is the real challenge.”
Frederick Mishkin (Columbia University)21
...Financial instability “occurs when shocks to the financial system interfere with information flow so that the financial system can no longer do its job of channeling funds to those with productive investment opportunities.”
Norges Bank22
“Financial stability means that the financial system is robust to disturbances in the economy, so that it is able to mediate financing, carry out payments, and redistribute risk in a satisfactory manner.”
Tommaso Padoa-Schioppa (European Central Bank)23
“...[financial stability is] a condition where the financial system is able to withstand shocks without giving way to cumulative processes, which impair the allocation of savings to investment opportunities and the processing of payments in the economy. 20 See Large (2003).
21 See Mishkin (1999).
22 See Norwegian Central Bank (2003).
23 See Padoa-Schioppa (2003).
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“The definition immediately raises the related question of defining the financial system...[which] consists of all financial intermediaries, organized and informal markets, payments and settlement circuits, technical infrastructures supporting financial activity, legal and regulatory provisions, and supervisory agencies. This definition permits a complete view of the ways in which savings are channeled towards investment opportunities, information is disseminated and processed, risk is shared among economic agents, and payments are facilitated across the economy.”
Anna Schwartz (National Bureau of Economic Research)24
“A financial crisis is fueled by fears that the means of payment will be unobtainable at any price and, in a fractional reserve banking system, leads to a scramble for high-powered money. It is precipitated by actions of the public that suddenly squeeze the reserves of the banking system.... The essence of a financial crisis is that it is short-lived, ending with a slackening of the public’s demand for additional currency.”
Nout Wellink (De Nederlandsche Bank)25
“According to our own definition at the Nederlandsche Bank, a stable financial system is capable of efficiently allocating resources and absorbing shocks, preventing these from having a disruptive effect on the real economy or on other financial systems. Also, the system itself should not be a source of shocks. Our definition thus implies that that money can properly carry out its functions as a means of payment and as a unit of account, while the financial system as a whole can adequately perform its role of mobilizing savings, diversifying risks, and allocating resources. Financial stability is a vital condition for economic growth, as most transactions in the real economy are settled through the financial system. The importance of financial stability is perhaps most visible in situations of financial instability. For example, banks may be reluctant to finance profitable projects, asset prices may deviate excessively from their underlying intrinsic values, or payments may not be settled in time. In extreme cases, financial instability may even lead to bank runs, hyperinflation, or a stock market crash.”
24 Schwartz (1986).
25 See Wellink (2002).
References
Chant, John, 2003, “Financial Stability As a Policy Goal,” in Essays on Financial Stability, by John Chant, Alexandra Lai, Mark Illing, and Fred Daniel, Bank of Canada Technical Report No. 95 (Ottawa: Bank of Canada), September, pp. 3–4.
Crockett, Andrew, 1997, “The Theory and Practice of Financial Stability,” GEI Newsletter Issue No. 6 (United Kingdom: Gonville and Caius College Cambridge), 11–12 July.
Davis, Philip, 2002, “A Typology of Financial Instability,” Financial Stability Report 2 (Vienna: Österreichische Nationalbibliothek).
Deutsche Bundesbank (2003), “Report on the Stability of the German Financial System,” Monthly Report, Frankfurt, December.
Diamond, Douglas W., and Raghuram G. Rajan, 2001, “Liquidity Risk, Liquidity Creation, and Financial Fragility: A Theory of Banking,” Journal of Political Economy, Vol. 109, 2, pp. 287–327.
——— , 2001, “Banks, Short Term Debt, and Financial Crises: Theory, Policy Implications, and Applications,” Proceedings of Carnegie Rochester Series on Public Policy (Amsterdam: Elsevier Science),Vol. 54, No. 1, pp. 37–71.
Duisenberg, Wim F., 2001, “The Contribution of the Euro to Financial Stability,” in Globalization of Financial Markets and Financial Stability—Challenges for Europe (Baden-Baden: Nomos Verlagsgesellschaft), pp. 37–51.
Ferguson, Roger, 2002, “Should Financial Stability Be An Explicit Central Bank Objective?” (Washington: Federal Reserve Board).
Foot, Michael, 2003, “What Is ‘Financial Stability’ and How Do We Get It?” The Roy Bridge Memorial Lecture (United Kingdom: Financial Services Authority), April 3.
Greenspan, Alan, 1999, “Do Efficient Markets Mitigate Financial Crises?” speech delivered before the 1999 Financial Markets Conference of the Federal Reserve Bank of Atlanta.
Haldane, Andrew, 2004, “Defining Monetary and Financial Stability” (unpublished; London: Bank of England), February.
Houben, Aerdt C.F.J., Jan Kakes, and Garry Schinasi, 2004, “Toward a Framework for Safeguarding Financial Stability,” IMF Working Paper 04/101 (Washington: International Monetary Fund) and DNB Occasional Paper (Amsterdam, Forthcoming).
Large, Sir Andrew, 2003, “Financial Stability: Maintaining Confidence in a Complex World,” in Financial Stability Review (London: Bank of England), December, pp. 170–74.
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Mishkin, Frederick, 1999, “Global Financial Instability: Framework, Events, Issues,” Journal of Economic Perspectives, Vol. 13 (Fall), pp. 3–20.
Norwegian Central Bank, 2003, Financial Stability Review, February.
Padoa-Schioppa, Tomasso, 2003, “Central Banks and Financial Stability: Exploring the Land In Between,” in The Transformation of the European Financial System, ed. by Vitor Gaspar and others (Frankfurt: European Central Bank), pp. 269–310.
Schinasi, Garry J., 2003, “Responsibility of Central Banks for Stability in Financial Markets,” in Current Developments in Monetary and Financial Law—Volume 2 (Washington: International Monetary Fund), Chapter 17.
——— , 2004, “Private Finance and Public Policy,” IMF Working Paper 04/120 (Washington: International Monetary Fund).
Schwartz, Anna J., 1986, “Real and Pseudo-Financial Crises” in Financial Crises and the World Banking System, ed. by Forrest Capie and Geoffrey E. Woods (New York: St. Martin’s Press).
Truman, Edwin, 2003, Inflation Targeting in the World Economy (Washington: Institute for International Economics).
Wellink, Nout, 2002, “Current Issues in Central Banking”, (Oranjestad: Central Bank of Aruba), November 14.
Financial Regulation, Monetary Policy, and Inflation in the Industrialized World.pdf
Financial Regulation, Monetary Policy, and Inflation in the Industrialized World Author(s): Mark S. Copelovitch and David Andrew Singer Source: The Journal of Politics, Vol. 70, No. 3 (July 2008), pp. 663-680 Published by: The University of Chicago Press on behalf of the Southern Political Science Association Stable URL: http://www.jstor.org/stable/10.1017/S0022381608080687 . Accessed: 06/02/2015 10:59
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Financial Regulation, Monetary Policy, and Inflation in the Industrialized World
Mark S. Copelovitch University of Wisconsin – Madison David Andrew Singer Massachusetts Institute of Technology
This article argues that the institutional mandates of central banks have an important influence on inflation outcomes in the advanced industrialized countries. Central banks that are also responsible for bank regulation will be more sensitive to the profitability and stability of the banking sector and therefore less likely to alter interest rates solely on the basis of price stability objectives. When bank regulation is assigned to a separate agency, the central bank is more likely to enact tighter monetary policies geared solely toward maintaining price stability. An econometric analysis of inflation in 23 industrial countries from 1975 to 1999 reveals that inflation is significantly higher in those countries with central banks that are vested with bank regulatory responsibility, although this effect is conditional on the choice of exchange rate regime and the relative size of the banking sector. We also conduct a case study of the Bank of England, which lost its bank regulatory authority to a new agency in 1998. We find that the new Labour government under Tony Blair imposed the institutional change on the Bank of England in part to remove the bank stability bias from its monetary policymaking. These findings suggest that the mandates of central banks not only have important influences on macroeconomic outcomes, but may also be modified in the future by governments seeking to impose their own monetary policy preferences.
I n today’s world of global capital markets, political leaders face two primary challenges in regulating their economies. First, leaders must ensure the
stability of their country’s financial institutions. The frequency and magnitude of banking crises have reached levels not seen since the interwar period (Bordo et al. 2000). The United States, for example, experienced a dramatic bout of banking instability during the 1980s, with more banks collapsing in 1985–87 than in the prior 30 years (FDIC 1998). The United Kingdom faced a similar crisis among small banks during the 1970s, followed by the sudden and dramatic collapse of a prestigious bank in the mid- 1980s. Such episodes of financial instability have prompted governments to place ‘‘prudential regula- tion’’—rules and policies designed to ensure the solvency and soundness of banks and other financial institutions—at the top of their economic policy agendas (Eichengreen 1999; Llewellyn 1999). Second, politicians face the age-old challenge of fighting inflation—an economic scourge that has become even more virulent in today’s environment of floating exchange rates and full capital mobility (Mosley 2003). In nearly all industrialized countries, politi- cians have granted their central banks a high degree
of insulation from political pressures, leaving them ostensibly to focus on keeping prices stable.
The dual policy goals of financial stability and low inflation generate a challenge for monetary policy makers. The central bank’s main monetary policy instrument is the interest rate, which dampens infla- tionary pressures when raised. However, interest rate hikes are potentially harmful to banks’ profits and increase the probability of bank failures (Cukierman 1991; OECD 1992). A policy of financial stability may require a more gradual monetary tightening in the face of inflationary pressures, thereby allowing banks more time to adjust their balance sheets. On the other hand, a policy of strict price stability would require more aggressive interest rate adjustments. With one policy instrument and two potentially conflicting goals, a central bank must decide how much empha- sis to place on fighting inflation versus maintaining financial stability.
In this article, we focus on the institutional tension between the dual goals of financial stability and low inflation. Specifically, we argue that mone- tary policy makers have a less aggressive stance toward inflation when governments combine the bank regulatory- and monetary-policymaking functions
The Journal of Politics, Vol. 70, No. 3, July 2008, Pp. 663–680 doi:10.1017/S0022381608080687
� 2008 Southern Political Science Association ISSN 0022-3816
663
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within the central bank. Such ‘‘regulatory central banks’’—which exist in more than one-third of industrialized countries—have incentives to be espe- cially sensitive to the profitability and stability of the banking sector when setting monetary policy. We therefore argue that the presence of bank regulatory authority in the central bank’s mandate generates a bias in its monetary policymaking. On the other hand, in countries where bank regulation is assigned to a separate agency, the central bank is less likely to be biased by bank stability concerns and more likely to enact tighter monetary policies geared toward maintaining low inflation. Policy makers’ success in fighting inflation therefore varies with the institu- tional locus of bank regulatory authority.
We further argue that the effect of a central bank’s mandate on inflation is conditional on the govern- ment’s choice of exchange rate regime. Assuming full capital mobility, countries that adopt floating ex- change rates maintain the ability to conduct autono- mous monetary policy. Under such conditions, a central bank’s regulatory responsibilities play a signifi- cant role in shaping its monetary policy choices. In contrast, a central bank operating under fixed ex- change rates will not have the ability to pursue an independent monetary policy, and therefore its institutional features will be of little importance (O’Mahony 2007). We also test an ancillary hypothesis regarding the effect of the central bank’s regulatory mandate conditional upon the size of the domestic banking sector. We hypothesize that when banks represent a larger share of the national economy, a regulatory central bank will be particularly sensitive to bank stability when setting monetary policy.
In focusing on the relationship between central banks’ regulatory mandates and monetary policymak- ing, this paper contributes to two theoretical litera- tures in political economy. The first literature, which examines the politics of central banking, has focused overwhelmingly on the relative degree of political independence as the driving influence on the central bank’s monetary policymaking (e.g., Broz 2002; Clark 2002; Cukierman 1992; Franzese 1999; Grilli, Mas- ciandaro, and Tabellini 1991; Henning 1994; Max- field 1997). This literature depends critically on the implicit assumption that all central banks have the same responsibilities; thus, the ‘‘institutional struc- ture’’ of the central bank can be equated solely with its degree of insulation from the political whims of politicians (Bernhard, Broz, and Clark 2002).1
Politicians, who view monetary policy from the perspective of political expediency, will encourage a dependent central bank to adjust interest rates for political purposes (e.g., to provide a temporary boost to the economy before an election). In the absence of political interference, central banks are assumed to be aggressive inflation fighters.2 While we do not dispute the importance of a central bank’s political inde- pendence on its monetary policymaking behavior, we argue that the institutional locus of regulatory au- thority also strongly influences how central bankers make decisions—even for central banks with high degrees of independence. This argument essentially turns the central banking literature on its head: rather than assuming a uniform political influence on monetary policymaking, we argue that central banks can be pulled in different directions as a result of their institutional mandates.
The second relevant literature pertains to the dynamics of principal-agent relationships, specifically those that arise when elected governments delegate important tasks to bureaucratic agents. There are many studies of the challenges inherent in the dele- gation of authority to an agent whose preferences may differ from those of the principal and of the strategies available to principals to ensure the obedience of their agents (e.g., McCubbins and Schwartz 1984; Weingast 1984). The paper does not challenge this literature; instead, it illustrates how politicians’ initial choice to delegate multiple tasks to a single bureaucratic agency can have significant consequences for policy out- comes (Dewatripont, Jewitt, and Tirole 2000). The ‘‘multitask’’ dilemma exists in many policy domains, including environmental and energy policy, financial regulation, and health and safety. Consider, for example, the consequences of delegating responsibility for energy efficiency and environmental conservation to the same agency. If policies designed to minimize environmental damage have the side effect of raising energy costs, then an agent could find itself compro- mising one objective in favor of the other. A similar tension can be found in the mandates of financial regulators, who are frequently held accountable for the competitiveness and stability of the regulated industry. We apply this reasoning to central banks and examine how their anti-inflation policies might vary as a function of their regulatory responsibilities.
In the case of central banking in the developed world, governments generally decided their delega- tion structures in the early twentieth century, long
1Central bank independence is not always treated as a single analytical concept; see, e.g., Hallerberg (2002).
2For a discussion of central bankers’ preferences based on their varied career backgrounds, see Adolph (2005).
664 mark s. copelovitch and david andrew singer
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before the emergence of prudential regulation as a politically prominent issue. As regulation gained political salience, the preferences of regulatory central banks began to change. We note below that the mandates of central banks have been largely static over the years, but the evolution in the preferences of regulatory central banks has led some governments to alter their longstanding delegation decisions—specifi- cally by removing regulatory authority from the central bank—to ensure that monetary policy out- comes remain in line with government preferences.
The remainder of the article proceeds as follows. In the next section, we discuss the significant variation in the regulatory responsibilities of central banks, emphasizing that this variation has, until very recently, been entirely cross-national rather than intertemporal. We then explore the theoretical reasons why this variation in the central bank’s institutional mandate might influence its monetary policymaking choices, after which we move on to empirical tests of our argument. Using data from 23 industrialized countries from 1975 to 1999, we show that inflation has been systematically higher in countries where the central bank is vested with bank regulatory authority; as expected, however, we find that this effect is condi- tional on both the choice of exchange rate regime and the size of the domestic banking sector.
An important policy implication of this finding is that the removal of bank regulatory responsibil- ity from the central bank is a potential strategy for countries seeking to enhance the inflation-fighting credibility of their central banks. We test this logic by conducting a case study of the Bank of England, which lost its bank regulatory authority to the newly formed Financial Services Authority in a major British govern- ment initiative in 1998. We find that the new Labour government under Tony Blair was eager to control inflation and imposed the institutional change on the Bank of England in part to remove the bank stability bias from its monetary policymaking. Finally, we conclude with a discussion of the broader implications of these findings for our understanding of the politics of bureaucratic decision making.
Regulatory Responsibilities of Central Banks
Across the world, central banks vary in the responsi- bilities delegated to them by politicians. Central banks are generally responsible for implementing a country’s monetary policy by controlling the money supply and setting interest rates based on current economic
conditions. In addition, some—but not all—central banks serve as bank regulators with responsibility for implementing rules and restrictions on banking activ- ity, supervising compliance with prudential regulation and applicable laws, and otherwise safeguarding the stability of the banking sector. This variation has been understudied in the literature on the political econ- omy of inflation.3 Some scholars have examined the central bank’s regulatory mandate in the context of measuring its overall degree of independence from political pressures (Banaian, Burdekin, and Willett 1995). Other scholars have grappled with the inter- play between monetary policy and financial stability more generally (Cukierman 1991, 1992). However, in empirical analyses of inflation, central bank inde- pendence reigns supreme, and the central bank’s regulatory responsibilities are generally ignored.
The regulatory responsibilities of central banks are rooted in history. Until the early 1800s, the focus of central banks was predominantly on wartime finance. For example, the British government created the Bank of England in 1694 to raise funds for war and conquest (North and Weingast 1989). Norway’s central bank, the Norges Bank, was created in the wake of the Napoleonic Wars to stabilize the currency after a period of highly inflationary wartime expen- ditures (Capie, Goodhart, and Schnadt 1994). The exigencies of wartime finance eventually gave way to the more general goal of maintaining the internal and external value of the currency, which often involved ensuring convertibility in commodity-based exchange rate regimes. For many central banks, maintaining the value of the currency was closely intertwined with the regulation of the banking system, since commer- cial banks play a major role in the implementation of monetary policy (Capie, Goodhart, and Schnadt 1994). Central banks in countries such as Italy and the Netherlands gradually assumed bank regulatory responsibility in the twentieth century. The Bank of England operated for decades as an informal but powerful bank regulator and gained statutory author- ity to regulate banks with the Banking Act of 1979. In the United States, Congress created the Office of the Comptroller of the Currency—the regulator of na- tionally chartered banks—in 1863, but later delegated the statutory authority to regulate state-chartered
3An exception is Di Noia and Di Giorgio (1999), which offers mostly descriptive statistics and no theoretical argument. Posen (1995) includes the central bank’s regulatory mandate as part of a broader measure of financial opposition to inflation. In addition, there are several analyses of the pros and cons of separating the monetary-policy and regulatory functions, including Abrams and Taylor (2000); Barth et al. (2002); Goodhart (2001); Goodhart and Schoenmaker (1995); and Peek, Rosengren, and Tootell (1999).
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banks and bank holding companies to the U.S. Federal Reserve, founded in 1913.
In contrast, central banks and regulatory agencies emerged as completely separate entities in countries such as Canada and the Scandinavian countries. Canada, in fact, developed a bank regulator first—in 1925—and waited nine years before establishing its central bank in 1934. For countries such as Sweden and Norway, central banks have existed for centuries, yet bank regulatory authority lies with independent agencies subsequently established in the nineteenth and early twentieth centuries.4
Today there is considerable cross-national varia- tion in the institutional mandates of central banks. Of the 23 industrial countries listed in Table 1, 14 currently have separate central banks and bank regu- lators, while nine have unified systems. It is interesting to note that levels of central bank independence do not appear to be associated with regulatory structure. Countries with unified systems have central banks ranging from highly independent (Germany and the United States) to relatively dependent (Spain).
The regulatory responsibilities of central banks in industrialized countries have demonstrated very little variation over time. This path-dependent characteristic stands in marked contrast to other aspects of central banks, such as their degrees of political independence, which have experienced more frequent changes over time (see Bernhard 1998). Indeed, altering the institu- tional mandate of the central bank is costly, both politically and financially. To remove the regulatory responsibilities of the central bank, governments must enact highly detailed legislation to establish a separate bank regulatory agency with its own staff, budget, and bylaws. In the industrialized world, there are only three exceptions to the endurance of the central bank’s mandate: the United Kingdom and Australia, both of which transferred bank regulatory responsi- bilities to newly created separate agencies in 1998, and Iceland, which made a similar change in 1999.5 In the
overwhelming majority of cases, however, the regu- latory responsibilities of the central bank have re- mained steady through the years. This historical claim will prove important in our statistical analysis of inflation performance from 1975 to 1999, in which we assume that the central bank’s mandate is exoge- nously determined.
TA B L E 1 Location of Bank Regulatory Authority, Industrial countries (2005)
Central bank Separate agency
France1 Australia2
Greece Austria Ireland Belgium Italy Canada Netherlands Denmark New Zealand Finland Portugal Germany3
Spain Iceland4
United States5 Japan Luxembourg Norway Sweden Switzerland United Kingdom6
1The Banking Commission (Commission Bancaire) is a compo- site body chaired by the Governor of the Banque de France, with representatives from the Treasury. While the World Bank data classify this as a separated regime, we follow Goodhart and Schoenmaker (1995) in treating this as unification. However, our results are not sensitive to the alternative specification. 2Prior to 1999, the Reserve Bank of Australia regulated banks. This authority now resides with the Australian Prudential Regulatory Authority. 3The Federal Financial Services Supervisory Authority (Bunde- sanstalt für Finanzdienstleistungsaufsicht, BaFIN), established in 2002, united the three previously independent supervisory agencies for banking, securities, and insurance. BaFIN is en- trusted with control over the ‘‘sovereign measures’’ (licensing, issuing regulations) whereas the Bundesbank only participates in the ‘‘operational tasks’’ of supervision (e.g., collecting and processing banks’ prudential returns). See Goodhart and Schoenmaker 1995, http://www.bundesbank.de/bankenaufsicht/ bankenaufsicht_bafin.en.php, and http://www.bafin.de/bafin/ aufgabenundziele_en.htm#n6. Goodhart and Schoenmaker clas- sify this arrangement as a separated regime, while the World Bank treats it as ‘‘unification.’’ We follow the former, but our results are not sensitive to the alternative specification. 4 Prior to 1999, the Bank Inspectorate was part of the Central
Bank of Iceland. It was merged with the Insurance Supervisory Authority into a separate entity, the Financial Supervisory Authority, on January 1, 1999 (http://www.invest.is/files/ 2075240179Financial_System.qxp.pdf). 5The Federal Reserve is not the only bank regulator in the U.S., but it has overall responsibility for banks within the Federal Reserve system, and also regulates all bank holding companies. Note that our definition of ‘‘unification’’ is that the central bank has or shares responsibility for regulation. 6Prior to 1999, the Bank of England regulated banks. This authority has since been transferred to the Financial Services Authority.
4The Riksbank was established in Sweden in 1668, while the Royal Inspectorate of Banks was founded in 1907, and continues to operate today as the Swedish Financial Supervisory Authority (Finansinspektionen). In Norway, the Norges Bank was founded in 1816, while the Banking Inspectorate was founded in 1825; it operates today as the Banking, Insurance, and Credit Commis- sion under the Ministry of Finance.
5The new agencies are called the Financial Services Authority in the United Kingdom, the Australian Prudential Regulatory Authority in Australia, and the Financial Supervisory Authority in Iceland. Korea also experienced an institutional change in 1998, but it was not considered an industrial country for much of the time period of our analysis, and thus is not included in our sample.
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Central Banks, Regulation, and Monetary Policy Bias
Scholars of monetary policymaking have long argued that the central bank faces dueling pressures to keep prices stable and to maintain economic growth and full employment. The classic model by Barro and Gordon (1993) indicates a tension between maintain- ing inflation at a socially optimal level and respond- ing to political pressure to decrease unemployment. It is assumed that inflation aversion varies across countries. Consider the following quadratic loss function (adapted from Persson and Tabellini 2000):
L ¼ ½lðp � pÞ2 þðx � xÞ2�=2 ð1Þ
where p and x represent inflation and output (with overbars representing society’s preferred values), and l is the relative weight that the policy maker places on controlling inflation. The political economy liter- ature generally assumes that central bank independ- ence (CBI) is a useful proxy for l, with the expectation that politically insulated central banks will be more conservative, or inflation hawkish, than politically dependent ones.
While we do not dispute the importance of a central bank’s political independence on its monetary policymaking behavior, we argue that a sole focus on CBI ignores the fact that central banks also vary on another dimension: their regulatory mandates. Cen- tral banks responsible for bank regulation must respond appropriately to exogenous influences on the price level without triggering politically costly instability in the banking sector. When the central bank raises interest rates by decreasing the money supply, it deters investment and dampens aggregate demand, thereby keeping inflation in check. How- ever, interest rate changes motivated exclusively by expected changes in the price level have potentially adverse consequences for the profitability and sol- vency of banks (Cukierman 1991, 1992; Goodhart and Schoenmaker 1995).6 Banks are particularly vulnerable to changing financial market conditions because they must commit to loan terms in advance. More specifically, banks that issue fixed-rate loans, such as mortgages and certain corporate loans, will face declining profits as increasing interest rates force them to raise their own deposit rates. Bank customers might also withdraw their money in favor of higher-
yielding money market accounts or other invest- ments. The overall increase in the cost of funds, in turn, cuts into banks’ profits and increases the like- lihood of bank failures (OECD 1992). Increasing interest rates also leads to a greater risk of default by bank customers with flexible-rate loans, which also increases the potential for bank failures (OECD 1992; Tuya and Zamalloa 1994).7
The connection between monetary policy and bank stability does not inhere exclusively in the level and volatility of interest rates. A more general tension is that the cyclical effects of monetary policy and bank regulation push in opposite directions (Good- hart and Schoenmaker 1993). Monetary policy tends to move in countercyclical fashion: in the event of an economic slowdown, the central bank expands the money supply and provides more funds to speed up the economy’s recovery. However, the effects of bank regulation—especially prudential regulation, such as capital adequacy requirements—are procyclical, re- quiring a contraction of banking activity when the economy slows. For example, during a recession, a bank regulator might require an increase in loan-loss reserves and an improvement in the quality of banks’ lending portfolios. The resulting decrease in lending activity would result in tighter credit just as the monetary authorities were attempting to facilitate new lending to spur investment and consumption.
Examples of the tension between tight monetary policy and financial stability can be found across the developed and developing world. In New Zealand in 1985, a run on foreign exchange reserves prompted the central bank to increase interest rates dramati- cally, but concern over the soundness of the banking sector led to a reversal in policy and a prompt injection of liquidity (Healey 2001). In the United States, in 1979, Federal Reserve Chairman Paul Volcker announced that the Federal Open Market Committee (FOMC) would adopt a tight-money strategy called ‘‘nonborrowed reserve targeting,’’ in which changes in monetary aggregates such as M1 and M2—rather than interest rates or other eco- nomic targets—would serve as the target of monetary policy. When the LDC Debt Crisis began to unfold in 1982, policy makers and economists viewed the stringency of this approach as a contributing factor
6 For a similar argument about the vulnerability of the financial
sector to interest-rate defenses of fixed exchange rates, see Walter and Willett (2007).
7A drop in interest rates may also have adverse consequences for the banking system. If banks have loan portfolios that are more sensitive to interest rate fluctuations than their liabilities (e.g., treasury bonds and customer deposits), then a drop in interest rates—instigated by the central bank to spur economic growth or prevent disinflation—will lead to a deterioration in bank profit- ability in the short run. See Di Noia and Di Giorgio (1999).
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to the growing debt problems of the LDCs and the resulting instability of overexposed U.S. banks (Goodhart and Schoenmaker 1995). By the autumn of 1982, Volcker abandoned the FOMC’s sole focus on money supply targets in favor of inflation targets and other macroeconomic measures, which proved more sensitive to the plight of the banking sector. Finally, there are countless examples in the develop- ing world of national banking systems actively resist- ing the tight money policies of central banks during financial crises (Walter and Willett 2007). The central bank of Indonesia, for example, raised interest rates sharply in November 1997 in the wake of the Asian financial crisis, but quickly injected new liquidity into the economy as banks began to collapse (Boorman et al. 2000).
Given the tension between monetary tightening and bank stability, how will the central bank make monetary policy? Our central claim, which emanates from the earlier work of Cukierman (1991, 1992) and others, is that the presence of regulatory responsi- bility in the central bank’s institutional mandate introduces an important bias into its monetary policymaking calculus. When the central bank has official responsibility for regulating the banking sector, it is held publicly accountable in the event of bank failures or a sharp decline in bank profit- ability.8 For example, after the sudden collapse of Johnson Matthey Bankers (JMB) in the United King- dom in 1984, the Bank of England—which at the time was also the bank regulator—faced a barrage of criticism from Parliament. Indeed, the reappoint- ment of a prominent deputy governor of the Bank to another five-year term was delayed because of the negative fallout from the JMB affair (Singer 2007). It should come as no surprise that politicians find it politically expedient to castigate bank regulators for bouts of financial instability; in extreme cases, elected leaders will force the heads of regulatory agencies to resign. Any central bank with regulatory responsibil- ity will therefore be especially sensitive to short-term bank stability when making policy decisions.
In contrast, central banks without regulatory authority will, all else equal, base their monetary policy decisions on the price level, with less emphasis on the impact of interest rates on bank solvency or profitability. If banks become unstable, policy makers will place blame on the agency with official respon- sibility for bank supervision, such as Canada’s Office of the Superintendent of Financial Institutions or the
Australian Prudential Regulatory Authority. Central bank policy might be the focus of legislative discus- sion, but it is unlikely that the central bank itself will be held ultimately responsible if banks should fail. The U.S. savings and loan (S&L) crisis is illustrative: the rapid interest rate increases during the early 1980s squeezed the profit margins of S&Ls that issued long- term fixed-rate mortgages. Those S&Ls that did not take proper steps to rebalance their portfolios found themselves in dire financial trouble, and many collapsed altogether. The Federal Reserve, however, was not held publicly accountable for the S&L crisis despite the fact that its aggressive monetary policies were a contributing factor.9 Indeed, banks do not fail because of interest rate changes per se; they fail because of improper risk management, inadequate capital, or other forms of malfeasance—all of which are part of the bank regulator’s jurisdiction.
Returning to equation (1), our argument can be stated more formally: lr , ls , where the subscripts r and s refer to regulatory and separate central banks, respectively. In other words, separate central banks should be more inflation hawkish than regulatory central banks, all else equal. The discrepancy between lr and ls arises as a result of the varying principal- agent relationships between elected leaders and the central bank. When politicians delegate regulatory authority to the central bank, banking instability be- comes personally costly to central bankers. We there- fore expect central bankers to adjust their monetary policies with careful attention to bank stability.
Although we expect this logic to hold across countries and over time, it is important to acknowl- edge three important caveats to our argument. First, as noted previously, the influence of the institutional mandate of the central bank on inflation outcomes is likely to be conditional upon the prevailing exchange rate regime. Whether a country fixes or floats its exchange rate will influence the degree of monetary policy autonomy of the central bank. In a fixed exchange rate regime, the central bank has limited or no autonomy to set an independent monetary policy, and thus its characteristics—including its regulatory responsibilities—will have little impact on inflation outcomes (Bearce 2003; Oatley 1999; O’Mahony 2007).10
8For an example of this argument applied to the U.S. Federal Reserve, see Cukierman (1991).
9In contrast, Congress quickly dismantled the S&L regulator—the Federal Home Loan Bank Board—and fired its chairman.
10Central banks can employ sterilization as a monetary policy strategy in the short term, but this strategy is generally not viable in the medium- or long-term given the continual need to spend down foreign exchange reserves.
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Second, it is plausible that the influence of the central bank’s regulatory mandate on inflation out- comes is conditional on the size of the domestic banking sector. In particular, the central bank’s regulatory responsibilities might be more likely to influence the magnitude of l (the relative weighting given to inflation fighting) in countries where the banking sector is large relative to the overall size of the economy. The logic is straightforward: the size of the banking sector is an excellent proxy for the potential magnitude of the career costs associated with bank instability. In contrast, the central bank’s institutional mandate should have less of an impact on monetary policymaking when the banking sector is relatively small. As Figure 1 illustrates, there is significant variation in the size of the domestic banking sector across the advanced industrialized countries. While we believe the central bank’s regu- latory responsibilities are influential in all countries, we acknowledge the possibility that banking sector size may be an important determinant of the magni- tude of a regulatory central bank’s bias.
Finally, it is important to emphasize that no central bank ignores financial stability entirely. To be sure, the central bank is always concerned about the stability of the banking system, and bank stability factors into monetary policy regardless of the central bank’s additional responsibilities (Briault 1999). Cen- tral banks rely on the banking system for the smooth functioning of open market operations, and for the satisfactory supply of credit to the economy. Bank of England Governor Eddie George makes the case more
bluntly: ‘‘It is inconceivable that the monetary au- thorities could quietly pursue their [price] stability- oriented monetary policy objectives if the financial system through which policy is carried on . . . were collapsing around their ears’’ (George 1994). On this point we do not disagree; certainly no central bank would ever preside insouciantly over a faltering fi- nancial system. Rather, as depicted in equation (1), our argument is one of degree. Central banks without regulatory authority will place less emphasis on the negative externalities of bank stability in their policy choices, and more emphasis on fighting inflation. Thomas Cargill notes that ‘‘[t]he channels of conflict are fundamentally related to the need to have an economy-wide perspective for the conduct of mon- etary policy as opposed to an industry-wide per- spective for the conduct of financial regulation’’ (Cargill 1989, 60). Since monetary policy influences the objectives of financial regulation—namely bank stability—a central bank with regulatory power is expected to be more sympathetic to the perspective of industry than a central bank without regulatory authority.
Nevertheless, it is also important to note that the link between institutional structure and inflation could obtain even if central bankers make monetary policy decisions without actively taking their varying regulatory responsibilities into account. If market actors have expectations that the central bank might be influenced by the presence or absence of regu- latory responsibility, then they will react accordin- gly—setting wage contracts and locking in their
FI GU R E 1 Average Banking Sector Size, Industrialized Countries, 1975–99
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expected changes in the price level (Di Noia and Di Giorgio 1999; Goodhart and Schoenmaker 1995).
Our expectations of different policies as a result of central banks’ varying institutional structures are consistent with a variety of analytical approaches to regulation. Scholars such as Stigler (1971) argue that regulators are ‘‘captured’’ by the regulated industry, and enact policies that reflect the industry’s short- term needs. Central banks with regulatory authority (or ‘‘captured central banks’’) would therefore enact monetary policies more favorable to banks than central banks without regulatory authority. As Frieden (1991) notes, banks are generally considered to be a strong constituency in favor of price stability. How- ever, in the event of exogenous shocks, banks would prefer that the central bank take an ‘‘interest rate smoothing’’ approach—in which interest rates are increased in relatively small and steady increments— even if a more aggressive strategy would be more effective in controlling inflation (Cukierman 1991; see also Walter and Willett 2007). Other scholars argue that regulators safeguard their decision-making discretion and avoid policy choices that increase the chances of political intervention (Ferejohn and Shipan 1990; Singer 2004, 2007; Weingast and Moran 1983; Woolley 1984). Under this assumption, a central bank with regulatory responsibility would be especially sensitive to the threat of bank instability, since the legislature would likely react to bank failures with heightened monitoring of the central bank’s policies.11 In addition, our argument is consistent with the emerging literature on multitask incentive prob- lems in principal-agent theory (Dewatripont, Jewitt, and Tirole 2000). Agents with multiple responsibil- ities will behave differently than single-task agents, especially when there are potential conflicts between the agents’ tasks.
Empirical Analysis
Thus far, we have argued that a central bank’s regulatory mandate is an important yet underappre- ciated factor influencing its monetary policymaking behavior. In this section, we test this theory by exploring the relationship between the institutional locus of financial regulation—that is, whether the central bank has regulatory responsibility or not—
and inflation outcomes for a panel of 23 industrial- ized countries for the 1975–99 period. The empirical analysis follows the econometric specifications used in recent political economy work on inflation out- comes (Keefer and Stasavage 2002, Franzese 1999, Hall and Franzese 1998, Cukierman, Webb, and Neyapti 1992). The dependent variable is the (logged) five-year average inflation rate. Period averages are appropriate because many of the institutional deter- minants of inflation rates in our model, including the central bank’s mandate, change infrequently.12
The main explanatory variable, regulatory sepa- ration (hereafter Separate), is a binary variable that takes the value of 0 if the central bank holds or shares bank regulatory authority (unification) and a value of 1 if the task of bank regulation has been delegated to an agency separate from the central bank (separa- tion).13 Based on the theory explicated above, we expect this variable to be negatively associated with inflation outcomes—that is, countries that vest reg- ulatory authority in a separate agency should have lower inflation rates than countries that combine the two functions in the central bank. Data on Separate are compiled from a recently available World Bank dataset, Bank Regulation and Supervision, which assembles the results of a cross-national survey on the structure of financial markets and financial regulation (Barth, Caprio, and Levine 2003).14 We supplement the World Bank source with data from Goodhart and Schoenmaker (1995) and national monetary policy and regulatory policy authorities.15
In the first model, we include a standard battery of control variables, including central bank inde- pendence (CBI), exchange rate regime, trade open- ness, capital account openness, and the log of GDP and GDP per capita. Data on CBI are based on Cukierman’s (1992) methodology for calculating legal independence and are compiled from the Com- parative Political Dataset for the period 1975–96 (Armingeon et al. 2005) and Polillo and Guillen
11The policy literature on the institutional structure of central banks includes ‘‘increased politicization’’ as one of the disadvan- tages of vesting regulatory authority with the central bank. See, e.g., Barth et al. (2002).
12Inflation data are taken from the World Bank’s World Develop- ment Indicators.
13Note that the dependent variable does not take into account whether a single regulator oversees banking, securities, and insurance, or whether multiple agencies participate in bank regulation. Separate simply classifies the central bank’s partic- ipation in bank regulation. Data are taken from question 12.1 of the World Bank survey utilized by the authors to compile the dataset: ‘‘What body or agency supervises banks?’’
14 For complete background on the dataset, as well as the data
itself, see http://www.worldbank.org/research/projects/bank_ regulation.htm.
15See Table 1 for further details.
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(2003) for the remaining years.16 The exchange rate regime variable takes the value of 0 for floating or managed floating regimes and 1 for all varieties of ‘‘hard’’ fixed exchange rates (currency boards, monetary unions, hard pegs).17 Data are based on the International Monetary Fund’s classification of each country’s choice of exchange rate regime as published in the IMF’s Annual Report on Exchange Arrangements and Exchange Restrictions. Each obser- vation in the dataset is the average of the annual observations over the relevant five-year period.
Trade openness, measured as imports plus ex- ports as a percentage of GDP, is taken from the World Development Indicators database, along with GDP and GDP per capita. We also include the Chinn-Ito index of capital account openness (‘‘KAOPEN’’), in which higher values indicate greater degrees of openness (Chinn and Ito 2006). KAOPEN measures the extent of legal restrictions on cross-border financial transactions. It is based on the binary coding of restrictions in the IMF’s Annual Report on Exchange Arrangements and Exchange Restrictions and focuses on four dimensions of restrictions: the existence of multiple exchange rates, restrictions on the current and capital accounts (where the latter are measured as the proportion of the last five years without controls), and requirements to surrender export proceeds.18 The index has a mean of zero and ranges from -2.66 (full capital controls) to 2.66 (complete liberalization). We also include GDP to control for the significant disparity in size between the smallest industrialized countries (Luxembourg, Iceland, New Zealand) and the largest (United States, Japan, Germany). Likewise, including GDP per capita alle- viates our concerns that some of our institutional variables (e.g., CBI, KAOPEN) are merely proxies for different levels of development across the developed countries (Keefer and Stasavage 2002).
We include several additional controls. First, we add a variable that captures whether there was a currency crisis in the country during the four-year period. We also add a similar variable for the presence of a banking crisis. Data for both variables is taken from Glick and Hutchinson (1999), with missing data for Australia and the United States filled in using Caprio and Klingebiel (2003). Each of these variables is measured for individual years over the 1975–99 period, taking a value of 1 if there was a crisis and 0 otherwise. For each five-year period in the sample, each variable represents the sum of these individual year observations divided by five, thereby indicating the portion of time within each five-year period in which a crisis was occurring. All else equal, we expect inflation to be higher during periods that were more crisis-prone. Second, we include a dummy variable to capture whether a country has implemented explicit deposit insurance. Our expect- ation is that all central banks—regardless of their institutional mandates—have greater leeway to pur- sue price stability-oriented monetary policy when an explicit deposit insurance scheme protects depos- itors from losses in the case of bank failures. Data are taken from the World Bank’s Deposit Insurance Around the World database (Demirgücx-Kunt, Kar- acaovali, and Laeven 2005). Third, we include the size of the domestic banking sector, measured as domestic credit provided by the banking sector as a percentage of GDP. Data are taken from the World Bank’s World Development Indicators. Finally, we include a time trend variable that ranges from 1 to 5 in accordance with the five periods in the dataset. This variable controls for unobserved characteristics across each five-year period, including the factors that may have contributed to the secular decline in inflation rates across the developed world over the last 25 years.19
Models and Results
We first specify a basic linear regression (OLS) model with panel-corrected standard errors. This specifica- tion accounts for heteroskedasticity and spatial error correlation, common problems in time-series cross- sectional data that are evident in our sample (Beck
16Alternative CBI measures are available for only a subset of our sample; we therefore rely on Cukierman’s index. For a discussion of the challenges of measuring CBI, see Banaian, Burdekin, and Willett (1995).
17Alternative specifications using a 3-point ordered scale (float- ing, managed floating/intermediate, fixed) produce similar re- sults. Since we are primarily concerned with the distinction between ‘‘hard’’ pegs and other regimes, we utilize the simpler binary scale in the analysis that follows. The authors thank Nancy Brune for sharing her dataset, which draws on Bernhard and Leblang (1999) and compiles and codes the raw IMF data.
18For a detailed description of this measure, see Chinn and Ito (2006). 1975–79 data are missing for Switzerland and 1975–80 data are missing for the Netherlands; we use the 1980 and 1981 values, respectively, for these periods.
19In 1975–79, average inflation in the 23 industrialized countries was 12.02% per year. While average inflation rose slightly in 1980–84 (12.19%), it subsequently declined in each period (6.06% in 1985–89; 4.35% in 1990–94; 1.97% in 1995–99).
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2004; Beck and Katz 1995). The basic model is as follows:
Log Inflationit ¼ a þ bðIndependent VariablesÞit þ e
In our second model, we more directly assess the argument that the influence of the institutional struc- ture of the central bank (Separate) on inflation is conditional upon the exchange rate regime. When the exchange rate is fixed, the central bank will have limited or no autonomy to conduct an independent monetary policy, and thus the central bank’s institutional struc- ture should have little effect on inflation outcomes. We therefore include a multiplicative interaction term that captures the influence of Separate conditional upon the exchange rate regime. All else equal, we expect that a country which separates the bank regulatory authority from the central bank (Separate51) will realize lower inflation rates under floating exchange rates (Exchange Rate Regime50), since the central bank’s monetary policy autonomy increases and it will be free to pursue strict price stability. Under fixed exchange rates, how- ever, we expect Separate to have no significant effect on inflation outcomes, since the commitment to a fixed exchange rate commits all central banks—regardless of their regulatory mandates—to a price stability-oriented monetary policy. We therefore expect the interaction term to be positively associated with inflation outcomes.
Finally, in model 3 we test the argument that the influence of Separate on inflation is conditional not only on the exchange rate regime, but also on the size of the domestic banking sector. In this model, we therefore include a three-way multiplicative interac- tion, which captures the influence of Separate on inflation conditional on both the exchange rate regime and the banking sector size.
Table 2 presents the regression results for all three models, which are robust to alternative specifica- tions.20 In the models, several of the controls have the expected effects on inflation outcomes, including capital account openness and currency crises. The time trend variable is also significant and negative. Likewise, inflation rates are significantly lower in countries that choose fixed exchange rate regimes than those that pursue floating rates. Country size, as measured by GDP, is also associated with lower
inflation outcomes in model 3 but is not statistically significant in models 1 and 2. The remaining varia- bles appear to have had less impact on industrialized countries’ inflation rates during the 1975–99 period: trade openness, GDP per capita, deposit insurance, and banking crises are insignificant in all three models. Despite the extensive literature arguing that independence is the key institutional factor affecting
TA B L E 2 Regression Results
Dependent variable: ln(inflation) 1 2 3
GDP (log) 20.039 20.041 20.087** (0.050) (0.046) (0.042)+
GDP Per Capita (log) 20.067 20.068 20.006 (0.119) (0.106) (0.086)
Trade Openness 20.002 20.002 20.003 (0.002) (0.002) (0.002)
Capital Account Openness (KAOPEN)
20.271*** (0.043)
20.257*** (0.044)
20.250*** (0.044)
Deposit Insurance (1 5 yes)
0.077 (0.094)
0.11 (0.093)
0.12 (0.098)
Currency Crisis (1 5 yes)
0.720** (0.304)
0.689** (0.280)
0.597** (0.253)
Banking Crisis (1 5 yes)
0.103 (0.135)
0.057 (0.136)
0.034 (0.126)
Time 20.288*** 20.298*** 20.323*** (0.058) (0.058) (0.058)
CBI 0.361 0.493 0.246 (0.309) (0.308) (0.323)
Exchange Rate Regime (1 5 fixed)
20.281*** (0.087)
20.410*** (0.099)
20.751*** (0.227)
Banking Sector Size
20.004* (0.002)
20.003 (0.002)
20.001 (0.002)
Separate Central Bank
20.151** (0.071)
20.382*** (0.114)
20.037 (0.226)
Exchange Rate Regime * Separate
0.383*** (0.139)
0.131 (0.129)
Exchange Rate Regime * Banking Sector Size
0.003 (0.003)
Banking Sector Size * Separate
20.004** (0.002)
ER Regime * Banking Sector Size * Separate
0.003** (0.001)
Constant 4.826*** 4.849*** 5.553*** (1.631) (1.508) (1.428)
Observations 115 115 115 Number of countries 23 23 23 Log-likelihood 257.167 254.153 249.709 R2 0.809 0.819 0.832 Adjusted R2 0.786 0.795 0.805
Panel corrected standard errors in parentheses. *p , 5.10; **p , 5.05; ***p , 5.01.
20The results do not change substantively when including the ‘‘lagged dependent variable’’ (e.g., the previous five-year period’s inflation average) or when including period effects. Additional explanatory variables, such as union density, centralization and coordination of wage bargaining, veto players, the partisan composition of government, unemployment rates, GDP growth, and a dummy for an election year, also do not affect the basic results.
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central banks’ monetary policy behavior, CBI is also not significantly associated with lower inflation in our models. This finding could be attributable to measurement issues with CBI (e.g., Banaian, Burde- kin, and Willett 1995) or to theoretical problems with the link between CBI and inflation (e.g, Posen 1995).
In contrast, the results provide strong support for our argument that central banks’ regulatory man- dates are a key determinant of monetary policy- making and inflationary outcomes in the developed world. In the basic model, Separate is negative and highly significant. Since the significance of Separate in the interactive models is conditional on the exchange rate regime and banking sector size, we cannot directly interpret the regression coefficients in models 2 and 3 for these variables. However, F-tests of the joint significance of the interaction terms and their components in both models 2 and 3 are significant at the 1% level. We further analyze and interpret these interactive results below.
Given that the dependent variable in our model is the natural log of inflation, interpreting the magni- tude of these regression coefficients even in the ‘‘base’’ model is not straightforward. Therefore, in Table 3, we present first differences that illustrate the predicted effect of a one standard deviation (or equiv- alent relevant change) increase in each significant independent variable on average inflation, holding all other variables constant at their means.21 These re- sults further clarify the importance of a central bank’s regulatory mandate as a key determinant of inflation outcomes. All else equal, countries in which the central bank does not regulate banks (Separate51) have inflation rates that are 0.81 % lower than in ‘‘unified’’ (Separate50) countries. This effect is quite large in relation to both the average inflation rate in the industrialized countries from 1975 to 1999
(7.32%) and the predicted rate with all variables held at their means (5.38%).
Table 3 also illustrates the relative effect of the significant control variables from model 1 on infla- tion. A one standard deviation increase in capital account openness (KAOPEN), roughly equivalent to a shift from the mean level to its maximum, reduces inflation by 1.64%, a decrease of 30.5% from the predicted rate of inflation when all variables are set at their means (5.38%). Similarly, a shift in the time trend variable from period 2 (1980–84) to period 4 (1990–94) reduces inflation by 3.13%. This finding reinforces the observation that inflation throughout the developed world has declined sharply since the late 1970s. As expected, fixed exchange rates also reduce inflation: a shift from floating to fixed rates reduces average inflation by 1.57%. Currency crises, on the other hand, increase average inflation by 5.42%.
Although these results clearly support our basic hypothesis, they do not test our conditional argu- ment that the effect of Separate should depend on the choice of exchange rate regime. Thus, in Table 4, we present the relevant quantities of interest for the two-way interactive model (model 2). Here, too, the results strongly support our argument. Under float- ing exchange rates, separation of monetary policy- making and bank regulation significantly reduces inflation. When the central bank regulates banks under floating rates, predicted average inflation is 7.16%. However, when responsibility for bank regulation is assigned to a separate agency, average predicted inflation declines sharply to 4.28%. As the table illustrates, this is a statistically significant differ- ence at the 95% confidence level. In contrast, ‘‘sep- aration’’ has no significant effect on inflation outcomes under fixed exchange rates. Indeed, pre- dicted average inflation under fixed rates is almost identical in both ‘‘separated’’ and ‘‘unified’’ systems (4.29% to 4.33%, respectively). This result confirms
TA B L E 3 First Differences, Model 1* Predicted average inflation rate, all variables at mean: 5.38%
Variable Predicted change in
average inflation Interpretation of one standard deviation
(or equivalent) change in X
KAOPEN 21.64% 1.25 to 2.59 (maximum openness 5 2.65) Currency Crisis 5.42% 0 to 1 time 23.13% Time 5 2 (1980-84) to Time 5 4 (1990-94) Exchange Rate Regime 21.57% 0 to 1 Separate 20.81% 0 to 1
*All other variables held constant at their means
21Calculations done using the Stata post-estimation software CLARIFY (Tomz, King, and Wittenberg 2003).
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our expectation that the institutional structure of the central bank has clear and significant effects on monetary policymaking and inflation outcomes, but that this effect is conditional on the choice of exchange rate regime.
Finally, in Figures 2 and 3, we analyze and interpret the three-way interactive model (model 3), in which Separate is conditional on both the choice of exchange rate regime and the size of the domestic banking sector. In Figure 2, we graph the marginal effect of Separate under both fixed and floating exchange rates as banking sector size varies across the range of observed values in our dataset.22 As is evident from the chart, separation has no significant effect on inflation under fixed exchange rates, regard- less of the size of the banking sector (dashed line). In contrast, separation has a clear and significant neg- ative effect on inflation under floating rates, but only at mid- to high levels of banking sector size.23 This result further confirms our expectation that the regulatory mandate of the central bank has clear and significant effects on monetary policymaking and inflation outcomes, but it also further clarifies the conditional nature of this expectation. Figure 3 builds on this finding by graphing the predicted inflation level under separation (SEPARATE- 5 1) and float- ing exchange rates as banking sector size varies across the range of observed values in our sample. Once again, the large and significant negative impact of separation on inflation outcomes under this unique combination of conditions is clearly evident. As these results illustrate, the institutional structure of the
central bank has the most significant impact on monetary policymaking and inflation when two conditions are met: (1) A country is operating under floating exchange rates; (2) The banking sector represents a sizeable portion of the domestic macroeconomy.24
As a robustness check, we consider the possibility that selection into the ‘‘separate’’ category may not be exogenous to the explanatory variables in our data—or in other words, the same variables that explain variation in inflation outcomes also may explain a country’s initial decision to separate bank regulatory authority from the monetary policy author- ity. To address this concern, we use propensity score matching to ‘‘preprocess’’ our data (Ho et al. 2007; Leuven and Sianesi 2003; Simmons and Hopkins 2005). The critical idea behind propensity score matching is to match each ‘‘treated’’ observation (in this case, each country-year observation of ‘‘separation’’) with a ‘‘control’’ observation (i.e., a country-year observation of nonseparation) for which all the values of the explanatory variables are as close to identical as possible. The matching estimation results demonstrate that the paper’s main findings still hold after controlling for possible selection bias.25
A Case of Institutional Change: The Bank of England
As discussed earlier, governments in the industrial- ized world decided the regulatory responsibilities of their central banks many years ago, and those institutional configurations have been largely static over time. However, three industrialized coun- tries—the United Kingdom, Australia, and Ice- land—modified the mandates of their respective central banks in the late 1990s by transferring bank regulatory responsibility to newly created regulatory agencies. The argument presented above suggests that
TA B L E 4 Predicted Inflation by SEPARATE, Conditional on Exchange Rate Regime*
Exchange rate Regime
Does the CB regulate banks?
Predicted average inflation rate (%)
Confidence interval (95%)
Floating Yes (Separate 5 0) 7.16 6.18–8.28 No (Separate 5 1) 4.28 3.27–5.60
Fixed Yes (Separate 5 0) 4.29 3.49–5.28 No (Separate 5 1) 4.33 3.71–5.04
*All other variables held constant at their means
22 Table 6 was generated using the Stata code for analyzing
interactive terms developed by Brambor, Clark, and Golder 2006 (http://homepages.nyu.edu/~mrg217/interaction.html).
23The mean value of banking sector size in the sample is 90.4%, with a minimum of 27.0% and a maximum of 239.4%.
24The results for the size of the banking sector should be viewed with caution; while its marginal effect on inflation (given a separate central bank and a floating exchange rate) is statistically significant, the confidence intervals are fairly wide as a result of the small sample size. 25The results are available upon request by the authors.
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a government’s price-stability bias could lead it to alter the mandate of the central bank. In the follow- ing brief case study, we explore the applicability of our argument to the institutional evolution of the Bank of England in the United Kingdom. We find that price stability was a primary concern behind the modification of the Bank of England’s mandate, but that exogenous factors—namely the rise of financial conglomerates with multiple financial functions— were also an important influence behind the transfer of regulatory responsibilities to new all-encompassing ‘‘super regulator.’’ The case study demonstrates the possibility that governments in the future could be swayed to shift regulatory responsibility away from the central bank for price-stability concerns. At the same time, it also underscores the point that the central bank’s mandate is subject to exogenous (i.e., noninflation related) influences.26
Inflation, Regulation, and the Bank of England
In 1997, the incoming Labour government in the United Kingdom made an abrupt change in the mandate of the Bank of England. The new Chancellor of the Exchequer, Gordon Brown, announced that the Bank’s regulatory responsibilities would be transferred to a newly created financial regulator, the Financial Services Authority (FSA). In a separate announcement, Chancellor Brown also transferred full monetary policy authority to the Bank, thus
changing its status from an agent of the Treasury to a relatively independent central bank, similar to its counterparts in the industrialized world. These two policy initiatives were not unrelated; indeed, the preceding discussion about the conflicting mandates of central banks and bank regulators helps us to understand the rationale behind Brown’s actions.
The Bank of England faced a two-pronged challenge in the 1980s and 1990s. The first challenge was to maintain price stability in the face of increas- ing economic globalization and a turbulent foreign exchange market. The United Kingdom faced average annual inflation rates of approximately 10% between 1980 and 1984, and in excess of 5% through the mid- 1990s. In contrast, the United States kept average inflation below 8% between 1980 and 1984 and well below 4% through the mid-1990s.27 The United Kingdom’s struggle with inflation can be traced to its history of adopting and then abandoning a series of exchange rate regimes during the period after the fall of Bretton Woods (Bernanke et al. 1999). The most dramatic episode in Britain’s recent monetary history came in 1992, when currency speculators attacked the pound, leading to an abrupt devaluation and Britain’s hasty exit from the Exchange Rate Mechanism (ERM). In the absence of an exchange rate target, policy makers grew concerned about the credibility of monetary policy. Norman Lamont, then the Chancellor of the Exchequer, promptly an- nounced a temporary inflation target to guide the Treasury’s monetary policy decisions through the end of the current Parliament, with the understanding
FI GU R E 2 Marginal Effect of SEPARATE (0 to 1), Three-way interaction
FI GU R E 3 Predicted Values of Inflation by Banking Sector Size (with Separate Central Bank and Floating Exchange Rates)
26This case study draws upon a series of interviews conducted by the authors with regulators and financial consultants at the Bank of England, the Financial Services Authority, and private financial institutions in London during the summer of 2005. 27Inflation data taken from the World Development Indicators.
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that the next government—whether Conservative or Labour—would have to make a decision about the future course of monetary policy after the 1997 election (Bernanke et al. 1999).
The second challenge faced by the Bank of England pertained to bank regulation—and in particular, to the increasing prominence of bank instability. The Bank’s regulatory responsibilities evolved quickly in the 1970 and 1980s. During the 1970s, the Bank regulated informally, using ‘‘moral suasion’’ to keep commercial banks in line with its wishes (Penn 1989). However, the ‘‘secondary banking crisis’’ of 1973–75, in which a large number of community banks collapsed as a result of imprudent lending decisions and changing macro- economic conditions, prompted Parliament to grant the Bank formal regulatory responsibility in 1979. The Banking Act of 1979 established an authorization process whereby deposit-taking institutions were re- quired to secure a license from the Bank and undergo mandatory examinations by regulators. Just five years later in 1984, Johnson Matthey Bankers (JMB), a prestigious bank heavily involved in gold trading and real estate investment, became insolvent after a series of lending mishaps (Grady and Weale 1986). The col- lapse of JMB caused great embarrassment for the Bank, and led to another legislative initiative by Parliament: the Banking Act of 1987, which among other things created a bank supervisory board within the Bank and raised the profile of the Bank’s regulatory functions (Hall 1999).
In the wake of these episodes of financial insta- bility, the Bank quickly became a worldwide leader in the development of prudential regulations for com- mercial banks. Bank Governor Eddie George was instrumental in the creation of the 1988 Basel Accord, a capital adequacy standard for internationally active banks in the G-10 industrialized countries. At the same time, however, the large banks in the United Kingdom were finding new ways to take on risk, as manifested by the spectacular collapse of Barings in 1995. The country’s numerous smaller banks—in- cluding some 60 ‘‘building societies’’ which catered to local communities—were also struggling with the economic recession of the early 1990s (Logan 2001).
When the Labour Government came to power in 1997, it was clear that the Bank was being pulled in two different directions. On the one hand, the Treasury was adamant about reining in inflation through tighter monetary policy and increased credibility; on the other, the Bank itself was being held increasingly accountable for instability in the banking sector. Chancellor Gordon Brown’s strategy simultaneously addressed both challenges. In transferring operational
responsibility for monetary policy from the Treasury to the Bank, Brown enhanced the Bank’s independ- ence, bolstered the credibility of its inflation-fighting mandate, and signaled to the public a strong commit- ment to price stability. At the same time, by trans- ferring bank regulatory responsibility from the central bank to the newly created Financial Services Authority (FSA), the Government removed the potential bias that could compromise the Bank’s inflation-fighting mandate. In terms of fighting inflation, the combina- tion of increased independence and the removal of regulatory responsibility appears to have been suc- cessful: from 1999 to 2005, the United Kingdom’s average annual inflation rate was 2.38% and did not exceed 3% in any individual year.28
An alternative but complementary rationale for the removal of regulatory responsibility from the Bank was the increasing prominence of financial conglom- erates in London, and the corresponding challenges of orchestrating multiple functional regulators—including the Bank of England, the Securities and Investments Board (SIB), the Personal Investment Authority, and many others. Before the creation of the FSA, a large financial institution with banking, securities, and insurance arms could find itself subject to regulation and supervision from a welter of regulators, some of them with conflicting objectives. The new FSA, however, is a ‘‘super regulator’’ in that all forms of financial regulation—from insurance supervision to the prevention of securities fraud—fall within its jurisdiction. Proponents of the new agency argue that it leads to increased efficiency through economies of scale and that financial institutions are generally relieved to work with only one regulator with a unified set of rules and procedures (Briault 1999). According to this line of reasoning, the Government removed the Bank’s regulatory responsibilities in order to create a new, coherent financial regulator to manage London’s new financial conglomerates. It would have been impractical to grant the Bank the full respon- sibility for all of these regulatory functions. Some regulators also note that the Bank would be deemed far too powerful in the eyes of the Treasury if it was granted both political independence and a host of new regulatory responsibilities.29
While this alternative explanation for the change in the Bank’s mandate is attractive for its simplicity,
28Of course, it is impossible to determine whether the drop in inflation is attributable to the increase in independence, the removal of regulatory authority, or some other exogenous variable.
29We thank Andrew Bailey at the Bank of England for this point.
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it cannot explain the timing of the institutional change. Unlike the United States, in which the Graham-Leach-Bliley Act of 1999 relaxed a long-held prohibition against financial conglomerates, the United Kingdom’s experience with financial con- glomerates began in earnest in the 1970s and 1980s (Maycock 1986). Concerns about the inefficiency of multiple regulators and the blurring of lines between different sectors of the financial services industry therefore would have dictated an institutional change long before 1997.
Ultimately, the Bank of England case demon- strates the potential conflict between bank regulation and monetary policy. In 1997, the incoming Labour Government was eager to establish its inflation-fight- ing credentials after more than a decade of poor macroeconomic performance. The establishment of an independent central bank was an important first step, but the United Kingdom’s history of bank instability made it clear that the Bank’s responsibility for bank regulation could compromise its efforts to fight inflation. The transfer of bank regulatory authority to the FSA proved to be the capstone of the Government’s reengineering of monetary policy- making in the 1990s.
Conclusion
In this paper, we argue that a central bank’s institu- tional mandate—specifically, whether or not it also regulates banks—is an important determinant of its monetary policy decisions. The institutional locus of regulatory authority influences how the central bank resolves the tension between price stability and bank stability. All else equal, we argue that a central bank without regulatory responsibility is more likely to enact tighter monetary policies geared solely toward maintaining price stability. Analyzing data from 23 industrialized countries from 1975 to 1999, we find strong support for our argument: inflation rates have been significantly lower, on average, in countries where the central bank and the bank regulator are separate agencies. However, this effect of a central bank’s mandate on inflationary outcomes is condi- tional on both the choice of exchange rate regime and the size of the domestic banking sector. Under float- ing rates, the central bank’s regulatory responsibilities play a significant role in shaping its monetary policy choices, but only when the domestic banking sector is sufficiently large. In contrast, a central bank operat- ing under fixed exchange rates will pursue price
stability-oriented policies, regardless of its regulatory mandate or the size of the domestic financial sector. Thus, a central bank’s regulatory mandate influences monetary policy outcomes, but only under certain institutional and economic conditions.
These findings have several key policy and re- search implications. Above all, they suggest that our understanding of the political economy of central banks and monetary policymaking has been limited by an exclusive focus on independence as the primary institutional characteristic affecting central banks’ behavior. Indeed, as our results indicate, other facets of a central bank’s mandate—in particular, the scope of its regulatory responsibilities—also play a signifi- cant role in shaping its monetary policymaking decisions. This finding suggests that politicians should be cautious in assuming that granting the central bank operational independence will automati- cally enhance the credibility of its commitment to price stability, thereby resulting in lower average inflation. In many cases, central bank independence may indeed provide an ‘‘institutional fix’’ for the problem of high inflation. Whether or not this is the case, however, depends critically on the broader institutional mandate of the central bank, as well as on the structure of other monetary institutions (e.g., the choice of exchange rate regime) and the charac- teristics of the domestic financial system.
In addition, our findings about the influence of a central bank’s mandate on its policy choices shed light on a broader issue concerning the delegation of authority to bureaucratic agencies. In particular, they suggest that the behavior of agents in delegation situations depends critically not only on the type of tasks that the principal assigns them, but also on the number of tasks that they have been delegated (Dewatripont, Jewitt, and Tirole 2000). Specifically, they illustrate how politicians’ choice to delegate multiple tasks to a single bureaucratic agency can have significant consequences for policy outcomes. This is especially likely in cases where these policy goals (e.g., price stability and bank stability) are potentially conflicting, and bureaucrats have a pri- mary ‘‘tool’’ (e.g., interest rate manipulation) by which to achieve them. Thus, while it may be politically and administratively easier for politicians to assign multiple tasks to an existing bureaucracy rather than incurring the costs of creating a new agency, the bundling of multiple tasks within a single agency may produce unintended policy outcomes.
Finally, this paper also suggests an additional question for future research: what are the effects of institutional design on regulatory policymaking? Our
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argument has focused on the monetary policy im- plications of the institutional design of central banks, but there may be substantive differences in bank regulation as well. Are central banks more stringent bank regulators than stand-alone regulatory agencies? This question is beyond the scope of the literature on the political economy of monetary policy, but none- theless important for the expanding literature on comparative financial regulation (e.g., Rosenbluth and Schaap 2003). Exploring the relationship be- tween the mandates of regulatory agencies and key policy outcomes (e.g., financial stability, bank profit- ability) would further enhance our understanding of the ways in which institutions shape economic policy outcomes.
Acknowledgments
We thank Rob Franzese, Jeff Frieden, Alexandra Guisinger, Steven Hall, Lisa Martin, Bumba Mukher- jee, David Nickerson, Will Phelan, Naunihal Singh, and three anonymous reviewers for helpful com- ments and suggestions. An earlier version of this paper was presented at the 2007 annual meeting of the Midwest Political Science Association.
Manuscript submitted 17 April 2007 Manuscript accepted for publication 11 August 2007
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FINANCIAL STABILITY AND MONETARY POLICY INTERNATIONAL SURVEILANCE.pdf
FINANCIAL STABILITY AND MONETARY
POLICY: NEED FOR INTERNATIONAL
SURVEILLANCE
Gary Hufbauer* and Daniel Danxia Xie**
ABSTRACT
In this article, we propose a new monetary framework that defines a broader
set of assets, De Facto Money (DFM), as the benchmark for improving
financial stability. DFM is defined as traditional monetary aggregates plus
other liquid assets such as stocks and bonds. Empirical evidence for the
USA, other Organisation for Economic Co-operation and Development
countries, and a few emerging countries lends strong support for the con-
nection between exceptionally fast growth of DFM and subsequent financial
instability. We recommend several potential policy instruments to implement
the new monetary framework. Due to cross-country spillovers from national
financial crises, we suggest that international surveillance will be necessary to
monitor DFM and thus the underlying conditions for financial stability in
major countries. We argue that the International Monetary Fund is the ideal
institution to carry out this task in terms of its reputation and expertise.
I. INTRODUCTION
In the wake of the Great Crisis of 2008, regulatory proposals have empha-
sized the micro-prudential space: greater bank liquidity and more bank
capital, strict supervision of too-big-to-fail financial firms, ‘living wills’,
new resolution mechanisms, compensation that tracks risk. Proposed
reforms also address troublesome problems created by cross-border financial
institutions and international financial networks.
An important ingredient is missing from this menu. Micro-prudential
reforms that focus on financial firms are essential, but it is equally important
* Reginald Jones Senior Fellow, Peterson Institute for International Economics, Washington,
DC. E-mail: [email protected].
** Research Analyst, Peterson Institute for International Economics, Washington, DC when this
article was written. E-mail: [email protected].
The views expressed are the opinions of the authors, not necessarily the views of the Institute.
Journal of International Economic Law 13(3), 939–953 doi:10.1093/jiel/jgq035.
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to reform the macro-economic behavior of central banks. New evidence
shows a strong link between loose monetary policy and greater risk-taking
by banks and other financial institutions. Regulatory failures in the USA
and Europe may have been the proximate cause of the crisis, but massive
monetary policy errors set the stage.
In this article, we suggest that the monetary policy framework should be
expanded to take explicit account of financial stability as a policy objective
for central banks—a policy objective in addition to inflation and output.
To fulfill this objective, we commend a new measure of monetary aggregates,
De Facto Money (DFM). DFM attempts to measure the quantity of a broad
set of liquid assets, as a useful indicator of systematic financial risk in the
economy. Empirical evidence for the USA indicates that DFM can be useful
for identifying asset booms and moderating asset busts.
We also present cross-country evidence for the 2000s that shows the
connection between DFM and the international background of the Great
Crisis. For that exercise, a panel data set of 18 countries explores correl-
ations between the DFM dimension of monetary policy and current account
balances. The panel regressions indicate that loose monetary policies—
defined in terms of their wealth effects—are robustly related to current
account deficits. In their summit meetings, G-20 countries have stressed
that global imbalances should be curtailed to ward off the next crisis.
It follows that greater emphasis on financial stability, especially in the
boom phase of the economic cycle, should be explored as an instrument
for achieving this policy objective.
Monetary policy has historically belonged squarely in the realm of national
sovereignty, and has not been a subject of international surveillance. As US
Treasury Secretary John Connally famously said, when the Bretton Woods
system of fixed exchange rates was collapsing: ‘‘The dollar is our money
and your problem.’’ 1
As a consequence of the Great Crisis, however, the
downside risks of financial globalization now challenge the conventional
assignment of monetary policy strictly to national authorities. Cross-country
spillover effects call for surveillance of national monetary policies, especially
for ‘systemically important countries’.
II. BOOMING WEALTH AND PRIVATE RISK-TAKING
We are certainly not the first to critique the role of loose monetary policy,
during the period 2002–05, for setting the stage of the Great Crisis. John
B. Taylor was an early and prominent critic of the Federal Reserve. Taylor
1 John Connally made this comment to European finance ministers in 1971.
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used a simulation exercise to indicate that tighter monetary policy could have
slowed the huge housing boom in the USA. 2
In fact, well before the bubble, Bernanke and Gertler, 3
and then
Bernanke, Gertler, and Gilchrist proposed a ‘financial accelerator’ model
in which monetary policy pumps up the financial sector. 4
These research
papers illustrate how frictions within the credit markets can amplify shocks to
the macroeconomy. In good times, private actors underestimate risk, load up
on assets, and enlarge their debt burdens. In bad times, risk premiums soar,
and deteriorating credit market conditions worsen the economic downturn.
Borio and Zhu emphasized the explicit ‘risk-taking channel’ of monetary
policy—easier money by the central banks, higher risk by private lenders. 5
In a similar spirit, Rajan argued that loose monetary policy can induce asset
managers to ‘search for yield’, bending constraints such as contract struc-
tures and other institutional features. 6
Cukierman even mentioned Madoff as
an example of outright fraud facilitated by easy access to credit. 7
Seminal research by Jiménez et al. showed the impact of low interest rates
on the appetite of Spanish banks for credit risk. Under expansive monetary
policy, Spanish banks relaxed their lending standards and extended loans to
borrowers with weak credit histories. 8
2 John B. Taylor, ‘Housing and Monetary Policy’, http://www.stanford.edu/�johntayl/Housing%
20and%20Monetary%20Policy–Taylor–Jackson%20Hole%202007.pdf (visited 5 August
2010). 3
Ben Bernanke and Mark Gertler, ‘Agency Costs, Net Worth, and Business Fluctuations’,
79 American Economic Review 14 (1989). 4
Ben Bernanke, Mark Gertler and Simon Gilchrist, ‘The Financial Accelerator in a Quantitative
Business Cycle Framework’, in John B. Taylor and Michael Woodford (eds), Handbook of
Macroeconomics (Amsterdam: Elsevier, 1999) 1341–93. 5
Claudio Borio and Haibin Zhu, ‘Capital Regulation, Risk-Taking and Monetary Policy: A
Missing Link in the Transmission Mechanism?’, Bank for International Settlements Working
Papers No 268, December 2008, http://www.bis.org/publ/work268.htm (visited 5 August
2010). 6
Raghuram Rajan, ‘Has Financial Development Made the World Riskier?’, http://www.imf.org/
external/np/speeches/2005/082705.htm (visited 5 August 2010). Adrian and Shin carry the
analysis further and explore connections between monetary policy and the cyclical behavior
of the balance sheets of financial institutions. Tobias Adrian and Hyun Song Shin, ‘Money,
Liquidity, and Monetary Policy’, 99 American Economic Review 600 (2009). Tobias Adrian
and Hyun Song Shin, ‘Financial Intermediaries and Monetary Economics’, in Benjamin
Friedman and Michael Woodford (eds), Handbook of Monetary Economics (North Holland,
2010). 7
Alex Cukierman, ‘Reflections on the Crisis and on its Lessons for Regulatory Reform and for
Central Bank Policies’, Journal of Financial Stability (2010), http://www.tau.ac.il/�alexcuk/pdf/
Bocconi-Revised%20&%20Expanded-12-09.pdf (visited 4 November 2010). 8
Gabriel Jiménez et al., ‘Hazardous Times for Monetary Policy: What do Twenty-Three Million
Bank Loans Say About the Effects of Monetary Policy on Credit Risk-Taking?’, Bank of Spain
(Banco de España) Working Papers No 0833, http://www.bde.es/webbde/Secciones/
Publicaciones/PublicacionesSeriadas/DocumentosTrabajo/08/Fic/dt0833e.pdf (visited 5 August
2010). Smaller Spanish banks were found to be more affected by loose monetary policy than
larger ones, at 8, http://www.bde.es/webbde/Secciones/Publicaciones/PublicacionesSeriadas/
DocumentosTrabajo/08/Fic/dt0833e.pdf
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The Bank for International Settlements (BIS) further confirmed the
risk-taking channel of monetary policy, using a large new cross-country
data set. 9
Drawing on this data set, Gambacorta found robust evidence
that the default probability for banks increased in countries where interest
rates remained low for a lengthy period prior to the crisis. 10
In their latest
research, Altunbas, Gambacorta, and Marques-Ibanez explored a detailed
database of European and American banks, and confirmed that enduring
low interest rates contributed to higher risk-taking behavior. 11
To round
out the story, Schularick and Taylor provide long-run historical evidence
of the linkage between fast credit growth and financial crises. 12
To summarize, an academic consensus is forming around the idea that
prolonged easy money can set the stage for financial crisis. Of course, central
bankers are quick to proclaim ‘not on my watch’. Bernanke is a prominent
example. 13
But these self-serving declamations are not turning the tide of
academic analysis.
III. THE MAINSTREAM MONETARY REGIME
The great inflation of the 1970s and early 1980s turned mainstream econo-
mists and central bankers alike into inflation hawks. New Zealand pioneered
the adoption of inflation targeting (IT) as its monetary policy framework in
1989. Since then, IT has been popularly adopted in both developed and
developing countries. In fact, IT has become the dominant monetary
regime, with various degrees of formality. Developed countries with explicit
targets often identify 2–3% as the desirable range of inflation: the UK uses
2.5%, Korea uses 2.5–3.5%, Sweden uses 2% (�1%) and Spain uses 2%.
With or without explicit targets, central bankers settled on the view that,
9 ‘International Banking and Financial Market Developments’, BIS Quarterly Review,
December 2009, http://www.bis.org/publ/qtrpdf/r_qt0912.htm (visited 5 August 2010). 10
Leonardo Gambacorta, ‘Monetary Policy and the Risk-taking Channel’, BIS Quarterly
Review, Special Features, December 2009, at 43, http://www.bis.org/publ/qtrpdf/
r_qt0912.htm (visited 5 August 2010). 11
Yener Altunbas, Leonardo Gambacorta and David Marques-Ibanez, ‘Does Monetary Policy
Affect Bank Risk-taking?’, BIS Working Papers No 298, March 2010, http://www.bis.org/publ/
work298.htm (visited 5 August 2010). 12
Moritz Schularick and Alan M. Taylor, ‘Credit Booms Gone Bust: Monetary Policy,
Leverage Cycles and Financial Crises, 1870–2008’, National Bureau of Economic Research
Working Paper No 15512, November 2009, http://www.jfki.fu-berlin.de/faculty/economics/
team/persons/schularick/Schularick__Taylor_Credit_Booms_Gone_Bust.pdf (visited 5 August
2010). 13
Speech of Ben Bernanke, ‘Monetary Policy and the Housing Bubble’, Annual Meeting of the
American Economic Association, Atlanta, Georgia, 3 January 2010, http://www.federalreserve
.gov/newsevents/speech/bernanke20100103a.htm (visited 5 August 2010).
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when inflation was acceptably low, all was well in the economic kingdom. As
Blanchard, Giovanni dell’Ariccia, and Paolo Mauro put the consensus:
we thought of monetary policy as having one target, inflation, and one instrument, the policy rate. So long as inflation was stable, the output gap was likely to be small and stable and monetary policy did its job . . . . There was an increasing consensus that inflation should not only be stable, but very low. . ..
14
Bernanke et al. published the first systematic study of IT and found that
IT countries typically enjoyed lower inflation, lower inflation expectations,
and lower nominal interest rates. 15
Moreover, temporary shocks to the price
level had a smaller ‘pass-through’ effect on inflation. Based on their findings,
Bernanke et al. list the following principles for an IT framework:
� Explicit central bank commitment to low and stable inflation as the
overriding objective
� Public disclosure of the official inflation target over a defined time
horizon
� Mechanisms that compel the central bank to comply with its commitment
A later study by Truman likewise reported that, after adopting this
‘benevolent’ monetary regime, IT countries generally achieved lower infla-
tion levels and higher gross domestic product (GDP) growth rates. 16
Before
the Great Crisis, nearly all empirical studies confirmed the fine performance
of IT.
This happy consensus was shattered by the events of 2008 and 2009.
Buiter for one argues that the narrow focus of monetary policy on IT dis-
tracted the authorities from the equally important goal of financial stability. 17
The former Chief Economist of the Central Bank of Iceland, Gudmundsson
confessed: ‘I was a great fan of IT. However, experience has brought
with it a better appreciation of the challenges that come with it. Iceland
was the first country that I am aware of to suspend IT because of a financial
crisis.’ 18
14 Olivier Blanchard, Giovanni dell’Ariccia and Paolo Mauro, ‘Rethinking Macroeconomic
Policy’, IMF Staff Position Note, SPN/10/03, 12 February 2010, at 3–4, http://www.imf
.org/external/pubs/ft/spn/2010/spn1003.pdf (visited 5 August 2010). 15
Ben Bernanke et al., Inflation Targeting: Lessons from the International Experience (Princeton,
NJ: Princeton University Press, 1999). 16
Section 3 of Edwin Truman, Inflation Targeting in the World Economy? (Washington, DC:
Peterson Institute for International Economics, 2003). 17
Willem Buiter, ‘The Unfortunate Uselessness of Most ‘‘State of the Art’’ Academic Monetary
Economics’, 6 March 2009, http://www.voxeu.org/index.php?q=node/3210 (visited 5 August
2010). 18
Már Gudmundsson, ‘Challenges to Inflation Targeting: Raising Some Issues’, BIS Papers No
51, http://www.bis.org/publ/bppdf/bispap51b.pdf (visited 5 August 2010).
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IV. THE POLITICAL ECONOMY OF FINANCIAL CRISIS
Conservative economists sometimes argue that financial crises are an
efficient way of wiping out weak companies, leading to a post-crisis boost
in productivity. This view does not sit well with a public that must bear the
cost of high unemployment and lost retirement wealth. In democracies, and
even in some autocracies, political pressures to arrest financial distress are
considerable. Central banks will, over time, reflect public preferences. In the
early 1980s, inflation was the major concern, and IT eventually became the
dominant monetary policy. In the early 2010s, financial stability looks like a
bigger concern and this may set the stage for a new approach to monetary
policy. As Feldstein points out:
The Fed has been subject to substantial, and I believe justified, criticism
for its failure to prevent the behavior in those institutions that contributed
directly to the recent financial crisis . . . . In the years before the meltdown that began in 2006 and 2007, Fed officials frequently indicated that bank
capital was quite adequate and not a cause for concern. 19
While central bank independence has come to be regarded as the Holy Grail
of monetary policy, the taxpaying public, unemployed workers, and impover-
ished retirees will all be heard when central bank errors contribute to financial
crises. 20
This suggests that Financial Stability—capital F, capital S—will be
added to IT as an explicit policy objective.
V. RETHINKING THE MONETARY POLICY FRAMEWORK
In an unpublished paper, Xie proposed that the new monetary policy frame-
work should reflect a broad definition of aggregate assets to track DFM. 21
DFM measures the quantity of all liquid assets in the economy, expressed in
the national currency unit, such as dollars, euros, yen, or yuan. The goal of
Financial Stability can then be defined in terms of moderating fluctuations in
DFM. In comparison with two or three decades ago, most assets are more
tradable and more liquid than they were owing to the creation of new finan-
cial products, advances in information technology, much lower transaction
costs, and a high degree of global financial integration.
19 Martin Feldstein, ‘What Powers for the Federal Reserve?’, 48(1) Journal of Economic
Literature 134 (2010). Feldstein goes on to recite a familiar list of remedies for Wall Street
excess (tighter supervision of the large bank holding companies, etc.). 20
Alberto Alesina and Andrea Stella, ‘The Politics of Monetary Policy’, National Bureau of
Economic Research Working Paper No 15856, April 2010, http://www.nber.org/papers/
w15856.pdf?new_window=1 (visited 5 August 2010). 21
Daniel Danxia Xie, ‘Beyond Inflation Targeting in the Post Crisis World: Towards a New
Monetary Regime’ (Unpublished mimeo, Peterson Institute for International Economics,
Washington, DC, 2009, on file with the authors).
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Thanks to these innovations, a growing proportion of assets have come to
share the attributes of traditional money (M1, M2, and M3). 22
Moreover,
the shadow banking system has grown so large that it rivals the traditional
banking system which is safeguarded by deposit insurance in many countries.
In a financial crisis, the absence of deposit insurance for a shadow bank
(think Northern Rock, Bear Stearns, and AIG) hardly means that the insti-
tution can be allowed to fail, wiping out creditors as well as shareholders.
Our proposal emphasizes Xie’s augmented measure, DFM, in order to
take account of the liquidity characteristics of a broad spectrum of assets,
including traditional bank assets, bonds and shares, real estate, and new
financial instruments (like mortgage-backed securities). Since different cate-
gories of assets have different degrees of liquidity, ideally we would like to
sum up the total of liquidity-weighted assets in the economy. Equation (1)
provides a simple definition of DFM:
DFM ¼ Xn
i¼1
Liquidityi � Vi ð1Þ
In equation (1), Vi denotes the total value of asset category i, and Liquidityi measures the degree of liquidity of this type of asset, on a scale from zero to
one. For example, bank deposits, certificates of deposit and money market
funds might have a liquidity index of 1.0, bonds might have 0.9, stocks 0.7,
and residential real estate 0.5.
To illustrate the calculation of DFM in the USA, we make the strong
assumption that all assets have the same degree of liquidity. This assumption
gives too much weight to real estate relative to stocks and bonds (even
though real estate is much more liquid now than it was two decades ago).
With this assumption we can borrow the wealth account data constructed by
Jorgenson, and Landefeld and Jorgenson. 23
The wealth account is the sum of
the reproducible and tangible assets held by households and non-profit or-
ganizations (NPOs), and the government. It includes an adjustment for the
net international investment position of the USA. Averaged over the decade
from 1990 to 2000, data shows that 39% of total US wealth was in equity,
bonds, and mutual funds, while 22% was in residential housing. Another
22 There are small variations in the definition of monetary aggregates for different countries, but
the definitions are very similar. For the USA, M1: The total of currency in circulation,
checking accounts, and currency held as bank reserves; M2: In addition to M1, bank savings
accounts, money market accounts, retail money market mutual funds, and certificates of
deposit under $100,000; M3: In addition to M2, all other Certificate of Deposit (CD)s,
time deposits over $100,000; institutional money market mutual funds; deposits of
Eurodollars, and repurchase agreements (repos). 23
Dale W. Jorgenson, ‘A New Architecture for the US National Accounts’, 55 (1) Review of
Income and Wealth 1 (2009); Dale W. Jorgenson and J. Steven Landefeld, ‘Blueprint
for Expanded and Integrated U.S. Accounts: Review, Assessment, and Next Steps’, in
Dale W. Jorgenson, J. Steven Landefeld, and William D. Nordhaus (eds), A New Architecture
for the U.S. National Accounts (Chicago: University of Chicago Press, 2006) 13–112.
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20% of US wealth was held by the government. For our purposes, wealth
held by the government is excluded. 24
Figure 1 plots the GDP growth rate, the inflation rate (measured by the
Consumer Price Index, or CPI), the M2 growth rate, and the growth rate of
private US wealth for the USA from 1973 to 2009. 25
We see no large
anomalies in the GDP growth rate or inflation rate between 1993 and
2006. However, the growth rates of M2 and wealth accelerated after 1993. 26
Period averages are summarized in Table 1. From Figure 1 and Table 1,
we can see that during the 2003–06 periods, GDP, CPI, M1 and M2
generally grew at slower speeds than during the 1996–99 period, and the
speeds were comparable to the 1992–95 averages. Note, however, the
unusual feature of the 2003–06 period: wealth growth reached 12.2%
annually, much faster than inflation or GDP. Column (6) shows the
difference between wealth growth rates and inflation rates; column (7)
shows the difference between wealth growth rates and GDP growth rates.
The period 2003–06 stands out among the past three decades. The
large gap between wealth growth and either inflation or GDP growth
indicates conditions leading to a crisis. Meticulous calculations by
Taylor likewise imply a deviation from the eponym Taylor Rule 27
from
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A nn
ua l
P er
ce nt
C ha
ng e
Real GDP CPI M2 Household & NPO Net Wealth
Figure 1. US growth rates of GDP, CPI, M2 and wealth, 1973–2009.
24 Government wealth, such as military bases, national parks and office buildings is highly
illiquid and plays little role in financial volatility. 25
Wealth figures from 2002 to 2009 are based on our own calculations. The source of the
figures for 1973-2001 is the Federal Reserve Board. 26
The growth of M3 also accelerated after 1993, but the Federal Reserve discontinued this M3
series in 2006. 27
The Taylor rule stipulates how much the nominal interest rate should be changed in response
to weighted divergences between: (i) the actual inflation rate and the target inflation rate; and
(ii) the actual level of GDP and the potential level of GDP.
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2003 to 2006. 28
However, excessive monetary ease shows up more clearly in
the gap between wealth growth and the sum of inflation and GDP growth
rates for this period, as shown in column (8).
VI. CROSS-COUNTRY COMPARISONS
Global imbalances are often cited as a factor contributing to the Great Crisis
(e.g. Bernanke), Obstfeld and Rogoff, and Bergsten and Subramanian). 29
Obstfeld and Rogoff offer the nuanced view that current account imbalances
‘magnified the ultimate causal factors behind the recent financial crisis’. 30
Table 1. US Growth Rates of GDP, CPI, M1, M2, and Wealth, 1977–2006
Periods GDP CPI M1 M2 Wealth Wealth�CPI Wealth�GDP Wealth�
(CPI + GDP)
(1) (2) (3) (4) (5) (6) (7) (8)
1977–81 3.1 9.8 7.4 8.8 12.2 2.3 9.1 �0.8
1982–91 3.0 4.1 7.6 6.8 7.5 3.4 4.5 0.4
1992–95 3.2 2.9 6.1 1.9 6.0 3.1 2.7 �0.1
1996–99 4.4 2.3 �0.1 6.2 11.3 9.0 6.9 4.7
2003–06 3.0 2.9 2.9 5.1 12.2 9.3 9.2 6.4
Source: U.S. Bureau of Economic Analysis, The Federal Reserve Board, and Jorgenson and
Landefeld (2006, 2009).
Note: For the purpose of this table, wealth is defined as the net worth of households and NPO
with an adjustment for the net international investment position.
28 See Taylor, above n 2; John B. Taylor, ‘The Financial Crisis and the Policy Responses: an
Empirical Analysis of What Went Wrong’, National Bureau of Economic Research Working
Paper No 14631, January 2009, at 5, http://www.nber.org/papers/w14631.pdf?new_window=1
(visited 5 August 2010). 29
Speech of Ben Bernanke, ‘Financial Reform to Address Systemic Risk’, The Council on
Foreign Relations, Washington, DC, 10 March 2009, http://www.federalreserve.gov/
newsevents/speech/bernanke20090310a.htm (visited 5 August 2010); Maurice Obstfeld and
Kenneth Rogoff, ‘Global Imbalances and the Financial Crisis: Products of Common Causes’,
http://elsa.berkeley.edu/�obstfeld/santabarbara.pdf (visited 5 August 2010); Fred Bergsten
and Arvind Subramanian, ‘America Cannot Resolve Global Imbalances on Its Own’,
Financial Times, 19 August 2009, http://www.iie.com/publications/opeds/oped.cfm?
ResearchID=1283 (visited 5 August 2010).
For a deeper debate about global imbalances, contrast the views represented by Obstfeld and
Rogoff, and Bergsten, who all think that large current account imbalances are not sustainable
in the long run, with the views supported by Dooley, Folkerts-Landau, and Garber and
Caballero, Farhi, and Gourinchas, as well as Cooper, who all argue that current account
imbalances can be a global equilibrium solution to differing savings and investment prefer-
ences in different countries, and can be sustained for long periods. Maurice Obstfeld and
Kenneth Rogoff, ‘Global Current Account Imbalances and Exchange Rate Adjustments’,
Brookings Papers on Economic Activity 1 (2005) 67–146. Michael Dooley, David
Folkerts-Landau, and Peter Garber, International Financial Stability: Asia, Interest Rates, and
the Dollar (New York: Deutsche Bank Global Research, 2005). Ricardo Caballero, Emmanuel
Farhi, and Pierre-Olivier Gourinchas, ‘An Equilibrium Model of ‘‘Global Imbalances’’ and
Low Interest Rates’ 98 American Economic Review 1 (2008) 358–93. Richard N. Cooper,
‘Living with Global Imbalances’, Brookings Papers on Economic Activity 2 (2007) 91–107. 30
See Obstfeld and Rogoff (2005), ibid, at 10.
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With this view in mind, it is worth exploring the relationship between
global imbalances and monetary policy. We start with a cross-region
comparison for the years before and during the Great Crisis. Due to the
lack of comparable data across countries, we simply use the total value of
bonds, equities, and bank assets (compiled from IMF Global Financial
Stability Reports) as an indicator of changes in DFM. Figure 2 illustrates
the experience in five emerging market areas. Emerging Europe registered
both the highest growth of DFM before the crisis and the deepest recession
afterwards. 31
Asset growth in emerging Europe was fueled by the bank lend-
ing channel, which empirically shows the highest correlation to an imminent
financial crisis.
Figure 3 shows the DFM experience of several developed countries from
2002 to 2008. Generally, the developed countries exhibit lower DFM vola-
tility and growth rates than emerging markets. While Greece was the cham-
pion in terms of DFM volatility and growth, Ireland, Spain, and the UK all
experienced significant DFM growth before the crisis.
Our data set for 18 Organisation for Economic Co-operation and
Development (OECD) countries includes as one crucial variable DFM, for
which our proxy measure is the total value of bonds, equities, and bank
assets (compiled from IMF Global Financial Stability Reports). 32
We use
-80
-60
-40
-20
0
20
40
60
80
2002 2003 2004 2005 2006 2007 2008
G ro
w th
o f
pe rc
en t
of G
D P
Emerging Asia Latin America Middle East Africa Emerging Europe
Note: Financial assets are defined as bonds, shares and bank assets.
Figure 2. Annual growth of financial assets in emerging markets, as percent of GDP.
31 See Morris Goldstein and Daniel Xie, ‘The Impact of the Financial Crisis on Emerging Asia’,
presented at the conference on Asia and the Global Financial Crisis, Santa Barbara, 18–20
October 2009, http://www.frbsf.org/economics/conferences/aepc/2009/09_Goldstein.pdf (vis-
ited 5 August 2010). 32
The database also includes current account data for the corresponding countries (from the
IMF WEO database).
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panel regression with so-called ‘fixed effects’ to control both omitted
variables and country-specific characteristics. 33
Column (1) of Table 2 shows the panel regression results where the cur-
rent account balance is the dependent variable, and the corresponding DFM
growth rate and its lagged value are independent variables. These empirical
results reveal a robust negative correlation between past DFM growth and
current account positions. Faster DFM growth in the lagged year is strongly
correlated with a larger current account deficit (or a smaller current account
surplus) in the present year.
Exchange rate movements may explain a good part of changes in current
account balances. To control for this effect, we single out the Euro area
countries and rerun the regressions. Since the Euro area countries have a
single currency, this experiment implicitly removes exchange rate changes.
-50
-40
-30
-20
-10
0
10
20
30
40
50
2002 2003 2004 2005 2006 2007 2008
G ro
w th
a s
pe rc
en t
of G
D P US
Japan
Germany
Greece
Ireland
Spain
U.K.
Note: Financial assets are defined as bonds, shares and bank assets.
Figure 3. Annual growth of financial assets in developed countries, as percent of GDP.
Table 2. Current Account Balance and DFM Growth Panel Regression 2000–08
Independent variables (1) (2)
18 OECD countries 12 Euro countries
Current year DFM growth rate 0.005 (�0.009) 0.008 (�0.012)
Lagged year DFM growth rate �0.024** (�0.01) �0.029** (�0.013)
Number of observations 108 72
Number of countries 18 12
Note: Standard errors in parentheses; **P < 0.05; P : Probability.
33 For an explanation of the ‘fixed effects’ regression model, see Jeffrey M. Wooldridge,
Econometric Analysis of Cross Section and Panel Data (Cambridge: MIT Press, 2001).
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Column (2) of Table 2 shows the new results: the negative effect of
prior-year DFM growth persists.
How can these results be explained? Domestic monetary expansion pushes
up asset prices and attracts more capital from overseas. A current account
deficit then needs to emerge to offset the capital inflow, as Harry Johnson
explained long ago. 34
An obvious channel for a rising current account deficit
is appreciation of the exchange rate—for those countries on flexible exchange
rate regimes. However, even for countries with fixed rate regimes—those in
the Euro area, for example—the negative relationship between DFM growth
and the current account balance persists. This implies that a second channel
is general economic expansion fueled by capital inflows, which in turn
enlarges the current account deficit. 35
An interesting piece of evidence to support the negative relation between
the current account position and lagged DFM growth is that China may
witness a smaller current account deficit in 2010. One explanation for this
surprising phenomenon could be the recent strength of housing prices due to
super-loose monetary policy in 2009.
VII. ALTERNATIVE MONETARY TARGETS
A few scholars and policymakers have begun to reconsider the received
tenets of monetary policy, in light of the most serious economic crisis
since the Great Depression of the 1930s. Blanchard dell’Ariccia, and
Mauro, for example, suggest the possibility of increasing the desired inflation
targets, aiming to make more room for monetary easing 36
in containing the
next economic crisis. 37
Other researchers have proposed revisions to the way in which inflation is
measured in the present IT framework. For example, they would include
selected asset prices in the price index to warn of the next bubble.
However, unlike consumption goods, the role of asset expansion cannot be
entirely captured by a price index. For example, new financial products may
be created that have little influence on the average level of asset prices, but
still greatly expand the gross value of tradable and liquid assets. Moreover,
financial innovation keeps creating new products that might be overlooked
by financial supervisors in the early stages and not integrated into the price
34 Harry G. Johnson, ‘The Monetary Approach to Balance of Payments Theory’, 7 Journal of
Financial and Quantitative Analysis 1555 (1972). 35
A caveat is that our panel data set only covers developed countries, which means that major
developing countries like China, India, and Brazil are not included due to the difficulties of
data collection. The experience of these developing countries may differ from the results
reported here. 36
To stimulate economic activity, central bank might reduce interest rates and boost money
supply. 37
See Blanchard, dell’Ariccia, and Mauro, above n 14, at 5.
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index until a crisis finally happens. Collateralized debt obligations (CDOs)
would be an example.
To achieve the policy objective of Financial Stability, in addition to IT,
additional policy targets and instruments are needed, not just an adjustment
of existing targets and instruments. As for targets, we have sketched DFM
and the way that the concept is summarized in equation (1) above is cer-
tainly measured better than we have done in this article.
Turning to instruments, various micro-economic controls are available,
in addition to the standard central bank suite of short-term policy interest
rates and M1 levels. For example, more stringent liquidity and capital
requirements for banks, beyond Basel II, are widely discussed, and these
can be varied in response to changes in financial stability conditions. An
obvious instrument for the housing sector is the mortgage down-payment
requirement. Margin requirements can be adjusted to moderate stock and
bond market booms. For derivatives, the authorities can insist on central
clearing houses, which in turn can enforce initial margin and variation
margin requirements. Another instrument is to regulate the extent of
credit card debt by imposing maximum interest rates, which in turn will
induce banks to raise their standards for issuing credit cards. 38
All these
tools are clearly within the legal powers of central banks and other financial
supervisors.
VIII. INTERNATIONAL SURVEILLANCE
If the new monetary policy framework we suggest is so good, and if instru-
ments for DFM targeting are readily available, why don’t countries by their
own initiative seek to moderate financial fluctuations by better control of
national DFM levels? What is the rationale for international surveillance?
Our short answer is that the combination of rising asset values and low
inflation is a central banker’s dream. Under the legendary Alan
Greenspan, years of loose monetary policy created a vast real-estate boom
that ended in tears. During the good times, Greenspan was crowned ‘the
greatest central banker in history’ by no less a figure than Alan Blinder. 39
The inevitable tears were confined neither to Wall Street nor the boundaries
of the US economy. Owing to global financial integration, damage was
38 Quite often, the credit card default rate is around 10 percent annually, which implies that
credit card interest rates must be at least 15 percent for the issuing firms to make money on
outstanding balances. On 30 April 2010, Senator Sheldon Whitehouse Democrat-Rhode
Island (D-RI) offered an amendment to the financial regulatory bill to force national card
issuers to comply with anti-usury laws in each state where their customers reside. If enacted,
this measure would dramatically curtail the issue of high-risk credit cards. In preference to
this approach, we favor granting the Federal Reserve the power to cap credit card interest
rates. 39
Alan S. Blinder, The Quiet Revolution: Central Banking Goes Modern (New Haven, CT:
Yale University Press, 2004).
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spread far and wide. In earlier but smaller episodes—the Latin American
debt crisis of the 1980s, and the Asian and Russian crises of the 1990s—
damage was also global.
National central banks are neither omniscient nor immune to the pleasures
of rising asset values. Moreover, national monetary authorities are unlikely to
give sufficient weight to the global consequences of ‘feel-good’ policies at
home. Even if central bankers are assigned explicit objectives—a combin-
ation of low inflation, full employment, and financial stability—they might
put insufficient weight on financial stability. From time to time, central
bankers need forceful warnings from their foreign peers.
For purposes of global financial stability, country size matters. A few large
countries bear nearly all the responsibility for stabilizing global asset values.
Any system of international financial surveillance needs to worry about the
USA, the EU, Japan, China, India, Brazil, and a very few others. This group
is the core of the G-20, the latest global steering group which came together
in the midst of the Great Crisis. 40
The empirical results derived in the last section suggest that international
trade and monetary surveillance are complementary actions. Obstfeld and
Rogoff, for example, have proposed that current account balances should be
a consideration in the formation of monetary policy. 41
According to our
empirical analysis, if excess monetary expansion is avoided, by adopting a
DFM target reinforced by international monetary surveillance, large and
persistent current account deficits could be mitigated.
At the G-20 Summit, held in London in April 2009, the Financial
Stability Forum of the BIS was enlarged to include all G-20 countries,
and renamed the Financial Stability Board (FSB), with the implication of
stronger powers and broader representation. However, so far the FSB has
only played a consultative role, with a focus on micro-prudential issues.
Despite its grand name, the FSB is not the right forum for international
surveillance of Financial Stability, in the sense that we conceive this
objective.
Instead the International Monetary Fund (IMF) is the prime candidate for
the task of macro-financial surveillance. The IMF already has extensive
experience in designing ‘early warning’ indicators. So far, however, the
IMF has been singularly ineffective in warding off looming financial crises.
Rather, the IMF’s role has historically been to discipline smaller countries
after a crisis erupts. We are suggesting that the IMF should widen its
40 The G-20 held its inaugural meeting in Washington in November 2008, with two meetings
since then – London in April 2009 and Pittsburgh in September 2009. The G-20 has essen-
tially eclipsed the G8 as the steering forum for the world economy. The next meetings are
scheduled for Toronto in July 2010 and Seoul in November 2010. 41
See Obstfeld and Rogoff (2005), above n 29, at 10.
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ambitions to play a ‘crisis avoidance’ role for ‘systemically important coun-
tries’, namely the big G-20 nations.
The DFM framework that we have proposed, with suitable refinements,
should be used by the IMF to monitor anomalous financial imbalances in
important countries and then blow the whistle. As a first step this would
require enhancement of the two IMF data reporting systems: the SDDS
(Special Data Dissemination Standard) and the GDDS (General Data
Dissemination System). Wealth accounts and flow of funds accounts would
be needed for the important IMF members. A benchmark threshold can
then be set between the DFM growth rate and a combination of GDP
and inflation growth rates, drawing on empirical evidence from previous
boom and bust episodes. When the DFM growth rate for an important
country exceeds the benchmark threshold, the IMF should sound the alarm.
IX. CONCLUSIONS
The Great Crisis has motivated both scholars and officials to think about
tools for containing the next global financial crisis. Loose monetary policy
was among the causes of the Great Crisis. At present, the mainstream mon-
etary policy regime, which focuses on price stability, is not well equipped to
detect the beginning of an asset bubble, which in turn sets the stage for a
financial crisis. The huge social cost of a financial crisis should, however,
compel policymakers to include Financial Stability as a major policy object-
ive. We propose the DFM framework, which quantifies a broad set of liquid
assets, as the basis for measuring Financial Stability. Empirical evidence
shows that DFM can anticipate conditions that presage a financial crisis.
Cross-country comparisons illustrate that future fragility is correlated to con-
temporary rapid expansion of DFM. Empirical evidence thus lends strong
support to including DFM as an additional target for central banks to moni-
tor, and thereby promote financial stability. To implement this new monetary
framework, central banks need to invoke more instruments than traditional
short-term policy interest rates and M1 controls. The new instruments must
include control over bank capital and liquidity requirements, mortgage down
payments, and maximum credit card interest rates.
Spillover of financial crisis is an inevitable side effect of globalization.
International surveillance is needed because national central banks typically
enjoy the upside of an asset cycle, and typically discount the negative spill-
over effects from a domestic crisis. The IMF is the ideal candidate to carry
out the surveillance task.
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Financial-progress-and-the-stability-of-long-run-money-demand-Implications-for-the-conduct-of-monetary-policy-in-emerging-economies_2009_Review-of-Fin.pdf
Review of Financial Economics 18 (2009) 124–131
Contents lists available at ScienceDirect
Review of Financial Economics
journal homepage: www.elsevier.com/locate/rfe
Financial progress and the stability of long-run money demand: Implications for the conduct of monetary policy in emerging economies☆
Ali F. Darrat a,⁎, Saif S. Al-Sowaidi b
a Department of Economics and Finance, Louisiana Tech University, Ruston, LA 71272, USA b Department of Economics, University of Qatar, Doha, Qatar
☆ An earlier draft was presented at the ERF 13th Ann (December 16–18, 2006) and was awarded “The Best Po to thank, without implicating, conference participants, t referees of this journal for useful comments and sugges ⁎ Corresponding author. College of Business, Louisian
71270, USA. Tel./fax: +1 318 257 3874. E-mail address: [email protected] (A.F. Darrat).
1058-3300/$ – see front matter © 2009 Elsevier Inc. A doi:10.1016/j.rfe.2009.04.003
a b s t r a c t
a r t i c l e i n f o
Article history: Received 15 August 2008 Accepted 2 March 2009 Available online 20 April 2009
JEL classification: E44 E58 E41
Keywords: Financial development Money demand instability Monetary policy Cointegration GCC region
This paper examines whether recent financial changes in three emerging market economies in the Gulf region (Bahrain, the UAE, and Qatar) have distorted the character and the stability of their underlying long- run money demand relations. Money demand instability prompts concerns about the appropriateness of targeting monetary aggregates and could weaken the presumed link between monetary policy and its ultimate objectives. Our results suggest that the quick pace of financial changes in the three emerging market economies did not cause undue shifts in their equilibrium money demand relations. Further evidence from direct tests of cointegration stability indicates the superiority of targeting M1 in the UAE and M2 for Qatar. In Bahrain, both M1 and M2 prove equally appropriate to guide monetary policy. Thus, despite the wave of financial developments that have recently swept the three Gulf economies, the evidence suggests that monetary authorities in these countries should maintain a close watch on monetary growth as a principal policy guide.
© 2009 Elsevier Inc. All rights reserved.
1. Introduction
Theory and evidence have long supported a significant role of a smooth-functioning financial market for promoting high and sus- tained economic growth [De Gregorio and Guidotti (1995), Levine (1997), Darrat (1999), and Darrat, Chopin and Lobo (2005)]. A well- developed financial market enhances growth by promoting a more efficient allocation of resources, encouraging a faster accumulation of physical and human capital and technological progress, and reducing production costs relating to transaction, information and monitoring.
Not surprisingly, financial markets in most emerging economies, including those of the Gulf Cooperation Council (GCC), have witnessed rapid expansion in recent years. Among the GCC countries, recent financial developments in Bahrain, Qatar and the UAE are particularly noticeable. These three countries have embarked on several reform measures in the last two decades, including facilitating the new entry of domestic and foreign banks, the gradual deregulation of lending and
ual Conference held in Kuwait licy-Oriented Paper”. We wish he Editor and two anonymous tions. a Tech University, Ruston, LA
ll rights reserved.
deposit interest rates, facilitating the use of credit and debit cards, updating payment technologies like ATM machines and electronic transfer of deposits, expanding a variety of internet banking services like e-banking and mobile banking technology, enhancing telecommunica- tions infrastructure, supporting their financial sectors with such measures like tax-free environment, stable and restriction-free exchange rate systems and solid regulatory environment. In their study of recent financial developments in the Middle East and North Africa (MENA) region, Creane, Goyal, Mobarak and Sab (2003) argue that Bahrain, Qatar and the UAE exhibit a significantly higher level of financial progress compared to other MENA countries.
While fast financial developments could promote economic growth, such developments may also hamper the effectiveness of monetary policy. Theoretically, financial development and the proliferation of new financial products and deposit substitutes could cause instability in the underlying money demand relationship with important consequences for the conduct and efficacyof monetary policy. This debate dates back to Gurley and Shaw's (1955) thesis that the emergence of new interest- bearing money substitutes resulting from financial developments may unexpectedly increase the interest-rate sensitivity of money holdings. Such elasticity shift in the money demand relation could weaken the presumed stable relation between monetary aggregates and the ultimate policy objectives of high economic growth and price stability. If valid, the Gurley–Shaw hypothesis casts serious doubts on the efficacyof monetary policy and calls into question the common use of monetary
Table 1 Descriptive statistics.
Variables Mean Std. dev. Min Max Skewness Kurtosis
Bahrain M1 5.79 0.45 5.17 6.92 1.15 0.62 M2 7.07 0.56 6.03 8.12 0.06 −0.74 X 7.54 0.40 6.83 8.44 0.50 −0.27 πe 4.22 7.45 −2.63 24.41 1.60 1.48
United Arab Emirates
M1 9.59 0.68 8.25 11.17 0.53 0.01 M2 10.96 0.68 9.47 12.30 −0.26 −0.24 X 11.75 0.39 10.97 12.70 0.34 0.29 πe 2.17 5.39 −6.77 13.86 0.32 −0.48
Qatar M1 8.30 0.39 7.46 9.41 0.70 1.84 M2 9.50 0.64 8.30 10.47 −0.69 −0.79 X 10.35 0.42 9.79 11.35 0.76 −0.55 πe 5.28 13.65 −20.78 33.95 0.33 −0.10 I 8.54 3.33 3.55 15.12 0.23 −1.07
M1=Log of real M1 in millions of local currencies, M2=Log of real M2 in millions of local currencies, X=Log of real GDP in millions of local currencies, πe=expected inflation (measured statically as the lagged inflation rate), I=the three-month Treasury Bill-rate in the United Kingdom (representing a foreign interest rate). The data are annual spanning the period 1973–2005.
125A.F. Darrat, S.S. Al-Sowaidi / Review of Financial Economics 18 (2009) 124–131
targeting in the conduct of monetary policy. As the conventional equation-of-exchange indicates, without a stable money demand (or velocity of money), there will be no predictable link between monetary aggregates and ultimate policy objectives. Indeed, there is some empirical evidence that further financial advancements in several developed countries in the late 1980s have destabilized their underlying money demand relationships [see, for example, Taylor (1987), Mulli- neux (1994), Mariscal, Trautwein, Howells, Arestis and Hagemann (1995), Hendry and Ericsson (1991), Ericsson and Sharma (1998), Gowland (1991), Arestis, Hadjimatheou and Zis (1992)].
To the best of our knowledge, this paper represents the first attempt to examine whether financial progress has distorted the long- run money demand relationships in the three Gulf countries and assess the implications for the operation of monetary policy in these countries.1 It can be reasonably argued that if fast financial develop- ments experienced by the three Gulf countries have not altered their long-run money demand models, then the relatively more sluggish financial developments in the rest of the GCC region (Kuwait, Oman and Saudi Arabia) would likely have had no effect on their long-run money demand equations either. We focus on the long-run money demand relations since a large and growing body of empirical research reveals that short-run money demand relations in both developed and developing economies are subject to unpredictable changes despite repeated efforts to adjust the estimated equations. Thus, the link between money growth and policy objectives over shorter periods has admittedly become tenuous at best. Consequently, the European Central Bank, and most recently the Bank of Japan, has exceedingly adopted longer-term monetary policy strategies.2
The rest of the paper is organized as follows. Section 2 outlines the methodology and data used. Section 3 reports the empirical results and provides some evidence of robustness. Section 4 offers concluding remarks and draws policy implications.
2. Research design and data
The empirical analysis begins with specifying appropriate long-run money demand equations for the three GCC countries which will then be tested if recent financial developments have caused significant instability in these functions. Measured in logarithms,3 a standard long-run money demand equation may take the form:
M=Pð Þt = α + βXt + γIt + δπ e t + εt
where M/P refers to real money balances defined as nominal money stock divided by the price level, X is real GDP (representing the budget constraint), I is nominal interest rates, πe is expected inflation, t stands for time, and ε is a white-noise disturbance term. Interest rates and expected inflation represent the opportunity costs of holding money balances rather than financial or physical assets, respectively. Theory predicts that βN0, but γb0 and δb0. Our data are annual observations covering the period 1973–2005, the longest period for which consistent data are available for all variables. The data come from the CD-ROM of the International Financial Statistics as well as from various publications of the Central Banks in the three Gulf countries. Table 1 provides a quick preview of the various variables in the three countries.
1 A few recent studies estimate money demand equations in the Gulf region but without any reference to the role of financial developments. See Harb (2004) and Lee, Chang and Chen (2008).
2 See The Economist (2006) and several research papers published by the Bank for International Settlements.
3 Money demand studies typically enter the variables in natural logarithms for convenience since this particular format smooth out the underlying variances thus inducing homoskedastic errors. Using natural logarithms also directly converts the estimated coefficients into elasticity measures.
Some technical issues regarding the proposed money demand equations for the three Gulf countries warrant a few comments. The first pertains to the particular definition of the money stock, M. This paper, like most other prior studies, reports the results from using two conventional measures of money stock; namely, the narrow M1 definition (currency with the public plus their demand deposits), and the broad M2 definition (M1 plus the public holdings of time and saving deposits). In the GCC countries, M1 is usually referred to as the “Money Supply”, while M2 is typically referred to as “Domestic Private Liquidity”.4 As to measuring expected inflation, we assume static expectations which allow the use of lagged inflation rates as a proxy for πe.
A second issue relates to the appropriateness of including some measures of interest rates in the money demand equations. Most prior research for developing economies suggests dropping the interest rate variable since financial assets (other than money balances) in these countries are seriously lacking. The little substitutability available be- tween moneyand other financial assets has effectivelylimited thechoice of domestic asset holders to either money or real goods. Consequently, consistent and reliable data on interest rate in most developing economies, including the GCC countries, are simply unavailable.
Therefore, most empirical studies on money demand in developing countries solely use expected inflation to represent the opportunity cost of holding money. However, another interesting, though unduly restrictive, aspect of most prior money demand studies is that they are also closed-economy models. Yet, holding foreign assets is a viable alternative to holding domestic money balances in most contempor- ary open economies (see Darrat, 1986). Since the three GCC countries have open economies with reasonably free capital mobility, this paper includes a measure of foreign interest rates in the money demand equations estimated. We use the short-term interest rate in the United Kingdom (the three-month Treasury-Bill rate) as a proxy for the international opportunity cost of holding domestic money in the GCC countries.5 Note that our money demand equations exclude the exchange rate variable for two main reasons. For most of the estimation period, currencies of the GCC countries are fixed relative
4 The Central Bank of the UAE also discusses in its official publications another measure dubbed “M3” defined as M2 plus “government” deposits. However, such a measure defies convention since, by definition, money stock should only include assets at the hands of the non-bank public (that is, outside banks and outside the government).
5 We also used the U.S short-term interest rate instead of the U.K. interest rate but the main conclusions remained unaltered. Note further that domestic nominal interest rates may embed the effect of expected inflation on money demand. However, our use of foreign interest rates minimizes this redundancy problem.
Table 2 Unit root test results.
Levels First differences
Variables WS ADF PP WS ADF PP
Bahrain M1 0.19 [3] 0.84 [2] 2.81 [2] −2.61 [2]⁎⁎ −2.37 [2] −24.29 [2]⁎⁎ M2 0.80 [3] 1.08 [4] 0.30 [4] −2.49 [4]⁎ −2.37 [4] −39.42 [4]⁎⁎ X 0.88 [5] 2.28 [6] 0.19 [6] −0.89 [2] −2.86 [6]⁎⁎ −25.66 [6]⁎⁎ πe −1.08 [2] −2.21 [4] −4.11 [4] −4.60 [2]⁎⁎ −2.46 [3] −29.67 [3]⁎⁎
United Arab Emirates M1 2.01 [1] 0.93 [1] −1.61 [1] −1.54 [1] −4.33 [1]⁎⁎ −11.42 [1]⁎ M2 2.06 [2] 0.49 [2] −2.14 [2] −0.49 [3] −5.83 [2]⁎⁎ −21.07 [2]⁎⁎ X 1.20 [2] 0.25 [2] 0.49 [2] −2.41 [2]⁎ −2.11 [2] −19.23 [2]⁎⁎ πe −2.92 [3] −2.63 [3] −25.24 [3]⁎⁎ −3.69 [3]⁎⁎ −3.75 [3]⁎⁎ −25.31 [3]⁎⁎
Qatar M1 −0.23 [2] −0.03 [2] −0.72 [2] −2.89 [2]⁎⁎ −2.78 [2]⁎ −21.72 [2]⁎⁎ M2 0.49 [2] −0.92 [2] −1.22 [2] −3.26 [2]⁎⁎ −2.63 [3]⁎ −21.61 [3]⁎⁎ X −0.01 [3] 0.12 [4] −4.18 [4] −3.81 [4]⁎⁎ −3.55 [4]⁎⁎ −33.30 [4]⁎⁎ πe −2.13 [2] −1.86 [3] −19.88 [3]⁎⁎ −1.11 [4] −5.40 [3]⁎⁎ −27.69 [3]⁎⁎ I −0.50 [4] −0.84 [2] −4.98 [2] −3.67 [3]⁎⁎ −4.14 [3]⁎⁎ −18.12 [3]⁎⁎
See notes to Table 1 for variable definitions. WS refers to the Weighted Symmetric test, ADF is the Augmented Dickey–Fuller test, and PP is the Phillips–Perron. Figures in brackets are the proper lag structures based on the Akaike Information Criterion (AIC). An ⁎⁎ indicates rejection of the null hypothesis of “non-stationarity” at the 5% level while an ⁎ indicates rejection of the null hypothesis at the 10% level. The test results consistently suggest that all variables across all three countries are stationary in first differences (that is, each is I∼(1)).
6 Recent studies have used the HJ procedure in a variety of contexts. For example, Darrat, Chopin and Lobo (2005) use the HJ procedure to examine the relative merit of simple-sum monetary aggregates versus Divisia money measures as a guide for the implementation of U.S. monetary policy; and Darrat and Zhong (2005) employ the H–J procedure to test the effect of the NAFTA accord on the degree of stock market linkages among the three North American countries.
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to the US dollar. As such, data on their exchange rate with respect to the US dollar do not exhibit sufficient variation over time to warrant empirical estimation. Even when some of the GCC countries announced that they were following the Special Drawing Rights (SDR) peg, they actually adopted a peg to the dollar. In addition, including both foreign interest rate and exchange rate could create serious multicolinearity since the two variables are theoretically related through the international Fisher effect.
Our main objective in this paper is to test whether the long-run money demand equations in the three GCC countries have been rendered unstable due to recent financial developments in these countries. Cointegration modeling, being a long-run apparatus, is particularly useful for the case at hand. If two or more variables possess a long-run equilibrium relationship, these variables are said to be cointegrated. Cointegrated variables are unlikely to drift apart permanently from each others, and when deviations from the equilibrium occur, stabilization forces within the system (called error–correction terms) will bring them back to equilibrium. We use the Johansen and Juselius (1990, JJ) procedure to test for the presence of significant long-run relations among real money demand (alter- natively defined) and its main determinants (real income, foreign interest rates and expected inflation).
For robustness, we use two different metrics to investigate whether financial developments have had any noticeable impact on the stability of long-run money demand relationships in the three Gulf countries. First, we introduce one or more (0, 1) dummy variables representing financial development episodes into the cointegrating systems to ascertain if these financial developments have exerted any significant impact on the underlying long-run (cointegrating) money demand relationships. We construct appropriate dummy variables for each country based on its particular experience with financial developments as we discuss in the next section. Adding the dummy variables to the cointegrated systems could either weaken or strengthen the underlying long-run relations, thus providing some insights into the impact of financial developments on long-run money demand equations. Several previous studies also use a similar dummy-variable approach to gauge possible shifts in cointegrated systems (see Hoffman & Rasche, 1991; Husted, 1992; Hafer & Kutan, 2003; Darrat & Zhong, 2005).
The second, and perhaps a more direct, procedure for examining the impact of financial progresss on the stability of long-run money demand relations makes use of the Hansen and Johansen (1993, HJ) technique of testing the stability of cointegrating vectors. Hansen and Johansen provide a formal testing procedure particularly designed for testing the stability (constancy) of cointegrating vectors in the context
of FIML estimations. Holding the short-run dynamics of the model constant at the full-sample estimates, the HJ procedure treats these estimates as the null hypothesis in consecutive recursive tests. In this way, any rejection of the null of cointegration stability should only arise from a breakdown in the long-run relation, rather than from any possible drift in the underlying short-run dynamics (Hoffman, Rasche and Tieslau, 1995).6
Prior research shows that the JJ approach, being based on the well- accepted likelihood ratio principle, is a robust technique for testing cointegration within multivariate time series models (Cheung & Lai, 1993; Gonzalo, 1994; Johansen, 1995). The JJ approach estimates the long-run attracting set in a VAR context that incorporates both the short- and the long-run dynamics of the multivariate model. In fact, Enders (1995) reports evidence favoring the JJ test over the more common two-step procedure of Engle and Granger (1987) even in bivariate models. Since results from the JJ test may be sensitive to the particular lag structures used in the underlying testing equations, we use the Akaike Information Criterion (AIC) to determine the proper lag profiles in conjunction with the added requirement that the resulting errors must also be serially uncorrelated. When testing for cointegration, Hakkio and Rush (1991) further suggest that the time span of the data should be sufficiently long to produce reliable cointegrating inferences. With over 30 years of data (1973–2005), the time span of our sample appears reasonable.
An important first step in any careful analysis of parametric models is to check the presence of unit roots (non-stationarity) in the data. A variable is said to be non-stationary if its stochastic properties (i.e., mean, variance, and covariance) vary over time. Generally, there are two reasons for checking non-stationarity of time series. First, Granger and Newbold (1974), Phillips (1986), and Stock and Watson (1989) demonstrate that if one or more of the variables in a given model have unit roots, the estimated regressions will likely be spurious (with inflated R-squares and biased test statistics like t- and F-ratios). Therefore, pre-testing for non-stationarity in time series data has become necessary to avoid spurious regressions. Second, and perhaps more relevant for this paper, testing for the presence of unit roots is also a prerequisite for cointegration testing. Only when the variables under examination contain unit roots will there be a need to check if these
Table 3-A1 The JJ cointegration test results for Bahrain.
λ-Max test Critical values Trace test Critical values
Null hypotheses Alternative hypotheses Test statistics (95%) (90%) Alternative hypotheses Test statistics (90%) (95%)
Panel A: Narrow money system (M1) Cointegrating vector: M1, X, π
e, I r=0 r=1 24.96 28.27 25.80 r≥1 45.26 53.48 49.95 r≤1 r=2 8.74 22.04 19.86 r≥2 20.30 34.87 31.93 r≤2 r=3 7.59 15.87 13.81 r≥3 11.56 20.18 17.88 r≤3 r=4 3.97 9.16 7.53 r=4 3.97 9.16 7.53
Panel B: Broad money system (M2) Cointegrating vector: M2, X, π
e, I r=0 r=1 21.51 28.27 25.80 r≥1 44.16 53.48 49.95 r≤1 r=2 12.21 22.04 19.86 r≥2 22.66 34.87 31.93 r≤2 r=3 6.03 15.87 13.81 r≥3 10.45 20.18 17.88 r≤3 r=4 4.41 9.16 7.53 r=4 4.41 9.16 7.53
See notes to Table 1 for variable definitions. The results from both test statistics (the λ-Max and the trace) consistently suggest no evidence for cointegrating (long-run) money demand relationships among real money stock (both M1 and M2), real GDP, expected inflation, and foreign interest rates. The JJ test statistics in this and all following tables are corrected for finite-sample biases using the procedure outlined in Reimers (1992).
Table 3-A2 The JJ cointegration test results for Bahrain after incorporating the possible impact of financial developments.
λ-Max test Critical values Trace test Critical values
Null hypotheses Alternative hypotheses Test statistics (95%) (90%) Alternative hypotheses Test statistics (90%) (95%)
Panel A: Narrow money system (M1) Cointegrating vector: M1, X, π
e, I r=0 r=1 37.14⁎ 37.85 35.04 r≥1 87.08⁎⁎ 81.20 76.68 r≤1 r=2 22.71 31.68 29.00 r≥2 49.94 56.43 52.71 r≤2 r=3 15.62 24.88 22.53 r≥3 27.24 35.37 32.51 r≤3 r=4 11.61 18.08 15.82 r=4 11.61 18.08 15.82
Panel B: Broad money system (M2) Cointegrating vector: M2, X, π
e, I r=0 r=1 38.24⁎⁎ 34.69 32.00 r≥1 85.43⁎⁎ 72.15 67.83 r≤1 r=2 26.92⁎ 28.49 26.08 r≥2 47.19⁎ 49.43 45.89 r≤2 r=3 11.80 21.92 19.67 r≥3 20.26 30.46 27.58 r≤3 r=4 8.46 15.27 13.21 r=4 8.46 15.27 13.21
See notes to Table 1 for variable definitions. D1and D2 are two shift terms approximating the impact of financial developments in Bahrain that began approximately in 1981 and 1993, respectively (see text for detail). The shift terms enter the cointegrating vectors exogenously. An ⁎⁎ indicates rejection of the null hypothesis of “no-cointegration” at the 5% level while an⁎ indicates rejection of the null hypothesis at the 10% level. The results from both test statistics (the λ-Max and the trace) consistently suggest strong evidence of cointegrating (long-run) money demand relationships among real money stock (both M1 and M2), real GDP, expected inflation, and foreign interest rates.
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variables share a common unit root (in which case they are said to be cointegrated)or they insteadhave uncommon roots (non-cointegrated).
Thus, we test for unit roots in each variable across the three Gulf countries. Again, these variables are real M1, real M2, real GDP, foreign interest rate, and expected inflation. We test for unit roots using three different procedures; namely, the Augmented Dickey–Fuller (ADF), the Phillips–Perron (PP), and the Weighted-Symmetric (WS) procedures. While theADF is a popular test of unit-roots, Pantula, Gonzalo–Farias and Fuller (1994) and Enders (1995) report compelling evidence in support of the relatively more powerful PP and WS tests. We use all three tests to ensure that our inferences regarding the important issue of data non- stationarity are unlikely driven by the particular testing procedure used.
3. Empirical results
3.1. Results from unit root and cointegration tests
We discuss below the empirical results from testing the presence of unit roots and cointegrating (long-run) relations between real money stock (alternatively measured) and the determinants of real money demand (real income, expected inflation and interest rates) for the three GCC countries.
Results from the ADF, PP and WS tests shown in Table 2 suggest that all variables across the three countries are non-stationary in levels, but become stationary when converted to first differences.7
7 Preferring to err on the conservative side, we determine our unit root inferences on the basis of at least two testing procedures.
These stationary findings are then used to formulate our cointegrating tests. That is, since the levels of the variables in each country exhibit unit roots, our next task is to check whether these variables (in levels) share one or more unit roots in which case they may be considered cointegrated. Recall that our main objective in this paper is to assess if financial developments in the three Gulf countries have had dis- cernable impact on their long-run money demand relations. Hence, we first test for the presence of a long-run money demand relation without allowing for financial developments, and then re-test the nature of the long-run relations after incorporating the shift terms representing these developments. Table 3-A1 displays the JJ test results of real M1 and real M2 systems for Bahrain without the shift terms, while Table 3-A2 does the same after introducing the shift terms in the two cointegrating vectors. Similarly, Tables 3-B1 and 3-B2 report the results for the UAE, and Tables 3-C1 and 3-C2 report the results for Qatar. Note that we have adjusted the Johansen–Juselius test statistics for possible small-sample biases using the correction procedure suggested by Reimers (1992). We also avoided possible biases from arbitrary lag specifications by using the AIC procedure to select the proper lag lengths in the testing models.8
The results for Bahrain in Table 3-A1 (with no allowance for financial developments) clearly show no evidence for a reliable cointegrating relation binding real money demand (however defined) and its main determinants (real income, expected inflation and
8 To conserve space, detailed coefficient estimates of the various cointegrating equations in the three countries are not reported here but are available from the authors upon request.
Table 3-B1 The JJ cointegration test results for the UAE.
λ-Max test Critical values Trace test Critical values
Null hypotheses Alternative hypotheses Test statistics (95%) (90%) Alternative hypotheses Test statistics (90%) (95%)
Panel A: Narrow money system (M1) Cointegrating vector: M1, X, π
e, I r=0 r=1 22.65 28.27 25.80 r≥1 54.24⁎⁎ 53.48 49.95 r≤1 r=2 17.61 22.04 19.86 r≥2 31.59 34.87 31.93 r≤2 r=3 9.16 15.87 13.81 r≥3 13.98 20.18 17.88 r≤3 r=4 4.81 9.16 7.53 r=4 4.81 9.16 7.53
Panel B: Broad money system (M2) Cointegrating vector: M2, X, π
e, I r=0 r=1 40.89⁎⁎ 28.27 25.80 r≥1 73.41⁎⁎ 53.48 49.95 r≤1 r=2 18.21 22.04 19.86 r≥2 32.51⁎ 34.87 31.93 r≤2 r=3 10.76 15.87 13.81 r≥3 14.30 20.18 17.88 r≤3 r=4 3.54 9.16 7.53 r=4 3.54 9.16 7.53
See notes toTable 1 for variable definitions. An ⁎⁎ indicates rejection of the null hypothesis of “no-cointegration” at the 5% level while an ⁎ indicates rejection of the null hypothesis at the 10% level. The results provide some evidence for cointegrating money demand relationships among real money stock (especially M2), real GDP, expected inflation, and foreign interest rates.
Table 3-B2 The JJ cointegration test results for the UAE after incorporating the possible impact of financial developments.
λ-Max test Critical values Trace test Critical values
Null hypotheses Alternative hypotheses Test statistics (95%) (90%) Alternative hypotheses Test statistics (90%) (95%)
Panel A: Narrow money system (M1) Cointegrating vector: M1, X, π
e, I r=0 r=1 38.20⁎⁎ 34.69 32.00 r≥1 82.65⁎⁎ 72.15 67.83 r≤1 r=2 24.09 28.49 26.08 r≥2 44.45 49.43 45.89 r≤2 r=3 15.74 21.92 19.67 r≥3 20.36 30.46 27.58 r≤3 r=4 4.63 15.27 13.21 r=4 4.63 15.27 13.21
Panel B: Broad money system (M2) Cointegrating vector: M2, X, π
e, I r=0 r=1 48.08⁎⁎ 34.69 32.00 r≥1 91.93⁎⁎ 72.15 67.83 r≤1 r=2 23.38 28.49 26.08 r≥2 43.85 49.43 45.89 r≤2 r=3 10.54 21.92 19.67 r≥3 20.46 30.46 27.58 r≤3 r=4 9.93 15.27 13.21 r=4 9.93 15.27 13.21
See notes to Table 1 for variable definitions. D1 and D2 are shift terms approximating the impact of financial developments in Bahrain that began approximately in 1981 and 1996, respectively (see text for detail). The shift terms enter the cointegrating vectors exogenously. An ⁎⁎ indicates rejection of the null hypothesis of “no-cointegration” at the 5% level while an⁎ indicates rejection of the null hypothesis at the 10% level. The results from both test statistics (the λ-Max and the trace) consistently suggest strong evidence of cointegrating (long-run) money demand relationships among real money stock (both M1 and M2), real GDP, expected inflation, and foreign interest rates.
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interest rates). This inference proves robust since it is confirmed by both versions of the JJ test (the λ-Max and the trace statistics) and that the null hypothesis of no-cointegration cannot be rejected even at the weaker 10% level of significance. However, as results in Table 3-A2 suggest, this finding for Bahrain is strongly overturned at the 5% level with both versions of the JJ test once the shift terms of financial progress are introduced into the tested vectors, and that this outcome reversal occurs for both M1 and M2 systems. Perhaps more importantly, introducing the financial progress shift term into the
Table 3-C1 The JJ cointegration test results for Qatar.
λ-Max test Critical values
Null hypotheses Alternative hypotheses Test statistics (95%)
Panel A: Narrow money system (M1) Cointegrating vector: M1, X, π
e, I r=0 r=1 21.67 28.27 r≤1 r=2 15.36 22.04 r≤2 r=3 3.14 15.87 r≤3 r=4 1.47 9.16
Panel B: Broad money system (M2) Cointegrating vector: M2, X, π
e, I r=0 r=1 30.22⁎⁎ 28.27 r≤1 r=2 17.42 22.04 r≤2 r=3 6.54 15.87 r≤3 r=4 3.67 9.16
See notes to Table 1 for variable definitions. An ⁎⁎ indicates rejection of the null hypothesis money demand relationship among real money stock (only M2), real GDP, expected inflation, in the case of M1 measure.
M2 system has also enhanced the stability of the cointegrating vector. This is because results from both JJ tests support two significant cointegration vectors in the real M2 demand relation. Having more than one significant cointegrating vector implies additional strengths for the underlying long run relation and suggests that the long-run relation is robust in more than one direction (see Dickey, Jansen, & Thornton, 1991).
Taken together, results for Bahrain strongly indicate that allowance for the financial innovation process is required to obtain significant
Trace test Critical values
(90%) Alternative hypotheses Test statistics (90%) (95%)
25.80 r≥1 41.64 53.48 49.95 19.86 r≥2 19.97 34.87 31.93 13.81 r≥3 4.61 20.18 17.88 7.53 r=4 1.47 9.16 7.53
25.80 r≥1 57.86⁎⁎ 53.48 49.95 19.86 r≥2 27.64 34.87 31.93 13.81 r≥3 10.22 20.18 17.88 7.53 r=4 3.67 9.16 7.53
of “no-cointegration” at the 5% level. The results provide evidence for a cointegrating and foreign interest rates. No evidence for a long-run money demand relationship exists
Fig. A-1. The HJ test results for stability of equilibrium real M1 relation in Bahrain.
Table 3-C2 The JJ cointegration test results for Qatar after incorporating the possible impact of financial developments.
λ-Max test Critical values Trace test Critical values
Null hypotheses Alternative hypotheses Test statistics (95%) (90%) Alternative hypotheses Test statistics (90%) (95%)
Panel A: Narrow money system (M1) Cointegrating vector: M1, X, π
e, I r=0 r=1 37.71⁎ 37.85 35.04 r≥1 79.07⁎ 81.20 76.68 r≤1 r=2 22.07 31.68 29.00 r≥2 41.37 56.43 52.71 r≤2 r=3 10.42 24.88 22.53 r≥3 19.30 35.37 32.51 r≤3 r=4 8.88 18.08 15.82 r=4 8.88 18.08 15.82
Panel B: Broad money system (M2) Cointegrating vector: M2, X, π
e, I r=0 r=1 40.21⁎⁎ 34.69 32.00 r≥1 81.17⁎⁎ 72.15 67.83 r≤1 r=2 20.57 28.49 26.08 r≥2 40.96 49.43 45.89 r≤2 r=3 13.57 21.92 19.67 r≥3 20.38 30.46 27.58 r≤3 r=4 6.81 15.27 13.21 r=4 6.81 15.27 13.21
See notes to Table 1 for variable definitions. D1 and D2 are shift terms approximating the impact of financial developments in Bahrain that began approximately in 1981 and 2003, respectively (see text for detail). The shift terms enter the cointegrating vectors exogenously. An ⁎⁎ indicates rejection of the null hypothesis of “no-cointegration” at the 5% level while an⁎ indicates rejection of the null hypothesis at the 10% level. The results from both test statistics (the λ-Max and the trace) consistently suggest strong evidence of cointegrating (long-run) money demand relationships among real money stock (both M1 and M2), real GDP, expected inflation, and foreign interest rates.
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long-run (equilibrium) real M1 and real M2 money demand equations. This implies that monetary policy-makers in Bahrain should take into account the impact of financial developments on money demand estimates when implementing their policy actions and this is necessary whether the Central Bank of Bahrain targets the narrow or the broad money stock.9
Similar conclusions emerge for Qatar and the UAE but in support of M1 demand instead. Specifically, the test results in Table 3-B1 for the UAE and in Table 3-C1 for Qatar do not reject the null hypothesis of no-cointegration in the case of M1 demand relation. However, as Tables 3-B2 and 3-C2 show, once the financial shift terms are introduced into the tested vectors, both versions of the JJ test consistently support the presence of significant long-run real M1 demand relations in both countries.
As to real M2 demand relations, the test results for the UAE and Qatar support the presence of potent long-run real M2 demand equations at the 5% level regardless of whether or not the shift terms are included (see Tables 3-B1, 3-B2, 3-C1 and 3-C2). Therefore, financial progress in both countries over the estimation period seems to have had no discernible impact upon their long-run real M2 demand relations. This finding accords well with Mehra (1989, 1992) who suggests that financial changes could distort the nature of the demand for M1 but not M2. In particular, he argues that the introduction of interest-bearing checkable deposits in the U.S. has made M1 balances an effective instrument for both transaction and saving purposes. Consequently, M1 balances become highly substitutable to the saving components of M2. In contrast, the broader M2 aggregate internalizes these substitutions, leading to a more well-behaved long-run demand relation. Overall, our empirical results imply that only the long-run real M2 demand relation remain unaffected in the face of financial progress in the UAE and Qatar. Such resilience of the long-run M2 demand relation to financial changes provides considerable support for using the broad (rather than the narrow) money stock as the primary target for monetary policy in both countries.10
9 Note that expected inflation in the M1 equation has an incorrectly signed coefficient. However, all coefficients in the M2 equation are correctly signed with reasonable value magnitudes similar to those reported in previous studies for other developing countries. This evidence implies some support for the use of M2 over M1 as the proper monetary policy target in Bahrain. 10 In an expanded version of this paper, we checked the temporal stability of the estimated parameters of the long-run money demand equations using the Chow and the Farley–Hinich tests. Keeping in mind the caveat regarding the difficulty of interpreting coefficients from cointegrating vectors, the test results suggest that all estimated coefficients in M1 and M2 equations proved temporally stable but only when shifts representing financial changes are incorporated into the equations. Detailed test results are available from the authors upon request.
3.2. Some evidence of robustness
To what extent are the above cointegration results robust? We checked the robustness of our results in two ways. First, one might argue that the money demand equations estimated in this paper for the three GCC countries could be improperly specified by using an incorrect measure of the budget constraint. This is because these countries are heavily dependant on oil production as their main source of national income and that oil revenues directly accrue to governments rather than to the private sector. Therefore, non-oil real GDP (rather than total real GDP) appears a more proper measure of the budget constraint in the public demand for money. Of course a counterargument is that a significant portion of the government revenue from exporting oil is injected into the private sector through government spending programs. Be that as it may, we checked the
Fig. A-2. The HJ test results for stability of equilibrium real M2 Relation in Bahrain. Notes: The curves depict recursive likelihood-ratio (LR) statistics based on the Hansen and Johansen's (1993, HJ) testing technique. The LR statistics are distributed as chi- squared, scaled at the 5% level of significance. The red dashed line at the value of one represents the 5% significance bound. Recursive statistics above (below) the unity line imply an unstable (stable) cointegrating space. (For interpretation of the references to colour in this figure legend, the reader is referred to the web version of this article.)
Fig. B-1. The HJ test results for stability of equilibrium real M1 relation in the UAE.
Fig. B-2. The HJ test results for stability of equilibrium real M2 relation in the UAE. Notes: See notes to Figs. A-1 and A-2.
Fig. C-2. The HJ test results for stability of equilibrium real M2 relation in Qatar. Notes: See notes to Figs. A-1 and A-2.
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sensitivity of all our results to using non-oil real GDP instead of total real GDP. It is both encouraging and reassuring that the results (available upon request) are qualitatively insensitive to this measure- ment issue.
Second, since the stability property of any estimated money demand relation is a critical requirement to ensure the usefulness of such a relation for policy purposes, we further examine the stability of the cointegrating vectors using the Hansen and Johansen (1993) formal test of parameter constancy designed specifically for cointegrating vectors. The HJ test is based on recursive likelihood-ratio statistics normalized by the 5% critical value. Calculated statistics that exceed the critical value imply rejection of the null hypothesis, suggesting an unstable cointegrating space. Naturally, the JJ test should be performed on those vectors that contain significant cointegrating relations according to the results from the JJ test reported earlier.
As Figs. A-1 and A-2 suggest, there is no evidence for a breakdown in the long-run M1 or M2 demand relations for Bahrain. Thus, results from the HJ test support our conclusions from the JJ test and provide another piece of evidence that both M1 and M2 possess significant and stable long-run money demand relations, making both monetary aggregates credible targets for monetary policy in Bahrain. However, different verdicts emerged from the HJ test for the UAE and Qatar. In the case of the UAE, results from the HJ test (see Figs. B-1 and B-2) suggest that only M1, once adjusted for financial changes, exhibits a
Fig. C-1. The HJ test results for stability of equilibrium real M1 relation in Qatar.
stable long-run demand equation. In contrast, the long-run relation linking real M2 to its main determinants show clear signs of instability even after including the shift terms representing financial progress into the cointegrating vector. The reverse is true in the case of Qatar. As Figs. C-1 and C-2 reveal, only the M2 long-run demand relation remain stable throughout the estimation period.11 Thus, the results suggest that monetary authorities in the UAE may need to focus on the narrow measure of money stock in formulating their policy actions, while it is advisable for Qatar's policy-makers to place more emphasis instead on the broad M2 money stock.12
4. Conclusion
This paper empirically examines the nature of long-run money demand relations in three emerging economies in the Gulf region (Bahrain, the UAE and Qatar). We focus on whether financial developments that these countries have experienced in recent years have distorted the character of their underlying equilibrium money demand relations rendering them structurally unstable. Substantial changes in the financial markets can impact transaction costs of holding money and could induce significant shifts between money and money substitutes. Therefore, the increased sophistication of financial markets may hinder the stability of the underlying long-run money demand relations. This prompts concerns about the appro- priateness of targeting monetary aggregates as a guide for monetary policy and whether monetary aggregates continue to possess the presumed tight relationship with the main policy objectives. Without a stable long-run money demand, monetary targeting to control inflation and promote economic growth would lose much of its appeal and itself becomes a source of economic disturbances.
Our results suggest that the quick pace of financial developments in the three emerging economies have not caused undue shifts in the equilibrium money demand relations. All three emerging economies continue to exhibit well-behaving and reliable long-run money demand equations, although simple adjustments in some of these equations are necessary to account for the process of financial developments. Thus, it appears that monetary targeting still repre- sents a proper long-run policy strategy in the three Gulf countries. However, additional evidence from direct tests of cointegration stability suggests the superiority of targeting the narrow M1 money stock in the UAE, while the evidence for Qatar supports the broader M2 money stock instead. As to Bahrain, both M1 and M2 exhibit reliable and structurally stable long-run money demand relations,
11 Recall that the M2 vector in Qatar displays significant cointegration even without the inclusion of the shift terms. This provides added support for the M2 equilibrium relation in Qatar. 12 It should not be surprising that countries differ in which measures of money prove stable since these countries do not have identical economic and institutional arrangements. Furthermore, as the famous Lucas critique has long pointed out, the demand stability of a money measure over a certain period of time does not guarantee that the same money measure will continue to provide credible forecasts in the future.
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making targeting either or both monetary aggregates an appropriate guide for monetary policy in Bahrain. In sum, the evidence we obtained suggests that monetary targeting is alive and well at least in the three emerging economies examined in this paper and that their Central Banks should maintain a close watch on money supply growth as a principal policy guide.
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- Financial progress and the stability of long-run money demand: Implications for the conduct of .....
- Introduction
- Research design and data
- Empirical results
- Results from unit root and cointegration tests
- Some evidence of robustness
- Conclusion
- References
Macroeconomic Stability, Financial Stability and Monetary policy.pdf
International Finance 15:2, 2012: pp. 205–224
DOI: 10.1111/j.1468-2362.2012.01302.x
Macroeconomic Stability, Financial Stability, and Monetary
Policy Rules∗
Pierre-Richard Agénor† and Luiz A. Pereira da Silva‡
†University of Manchester; Centre for Growth and Business Cycle Research; and FERDI (Fondation pour la Recherche et le
Développement International), and ‡Central Bank of Brazil
Abstract
This paper reviews arguments for and against attributing an explicit finan- cial stability objective to monetary policy. The discussion is conducted from the perspective of middle-income countries (MICs), where bank credit plays a critical role both on the supply and demand sides. It also discusses, on the assumption that a more proactive role is desirable, what monetary policy should react to and to what extent it should be combined with macropru- dential regulation. There are robust arguments in favour of monetary policy reacting in a state-contingent fashion to a measure at the private-sector credit gap, not only because of financial stability considerations but also
∗This paper dwells in part on some of our previous papers, including joint work with Koray Alper (Central Bank of Turkey). We are grateful to Koray Alper, Karim El Aynaoui, participants at the Inter-American Development Seminar for Central Banks and Finance Ministries (Washington, DC, 21–23 September 2011) and two anonymous referees for helpful discussions and comments. However, we bear sole responsibility for the views expressed here. A more detailed version of this paper is available upon request.
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206 Pierre-Richard Agénor and Luiz A. Pereira da Silva
because of the high degree of uncertainty regarding real-time estimates of the output gap in MICs. Nevertheless, monetary policy is not a substitute for macroprudential regulation; in particular, it cannot address the cross- section dimension of systemic risk.
I. Introduction
The global financial crisis has led to both a reassessment of financial regulatory systems worldwide and renewed calls for central banks to consider more ex- plicitly and systematically financial stability considerations in setting monetary policy. On the regulatory side, a number of proposals aimed at strengthening the financial system and encouraging more prudent lending behaviour in upturns have been put forward. In particular, it has been argued that by raising capital requirements in a contra-cyclical way, regulators could help to choke off asset price bubbles – such as the one that developed in the US housing market – before a crisis develops.1 Along these lines, and after months of internal debate, on 12 September 2010 the Basel Committee on Banking Supervision (BCBS) released a new capital framework, which not only strengthens the definition of capital but also recommends the implementation of both a capital conservation buffer and a countercyclical capital buffer.
On the monetary policy side, it has been argued that central banks should con- sider more systematically potential trade-offs between the objectives of macroe- conomic stability and financial stability.2 One reason for this is the growing concern among academics and policy makers that the achievement of price sta- bility may have been associated with an increased risk of financial instability. Indeed, it has been argued that financial imbalances may build up even in an environment of stable prices; low and stable rates of inflation may foster asset price bubbles, due for instance to excessively optimistic expectations about fu- ture economic prospects or to increased incentives to take on more risk. Thus, price stability may not be a sufficient condition for financial stability. At the same time, however, several observers have argued that trying to stabilize asset prices per se is problematic for a number of reasons – in particular because it is almost impossible to know for sure whether a given change in asset values results from
1 See Financial Services Authority (2009) and Brunnermeier et al. (2009). Agénor and Pereira da Silva (2010, 2012) offer a developing-country perspective.
2The debate actually predates the global financial crisis and initially focused on the extent to which monetary policy should respond to (or ‘lean against’) perceived misalignments in asset prices, such as real estate and equity prices, as opposed to ‘cleaning up after’. See Wadhwani (2008) for a review.
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changes in underlying fundamentals, non-fundamental factors, or both. Some observers have argued that, instead of getting into the tricky issue of deciding to what extent asset price fluctuations reflect changes in the economy’s fundamen- tals, central banks should focus on the implications of asset price movements for credit expansion and aggregate demand, and thus inflationary pressures.
This paper focuses on the second issue – the extent to which monetary policy should be concerned explicitly with financial stability objectives and, if so, to what financial indicators it should be made responsive. We do so in the context where macroprudential regulation is also a component of the policy framework aimed at preventing disruptive and costly financial crises.3 To conduct this analysis, and in contrast to much of the existing literature, we focus on middle-income countries (MICs) only. We do so for several reasons. First, financial markets in many of these countries remain underdeveloped. In most MICs, commercial banks continue to dominate the financial system.
Second, and related to the lack of financial diversification, bank credit has an important impact on the supply side of the economy. Firms borrow short term to finance their working capital needs (such as labor inputs and raw materials) prior to the sale of output. Third, the financial system in MICs is often highly vulnerable to small domestic or external disturbances. Abrupt reversals in short-term capital movements tend to exacerbate financial volatility.4 A number of studies have indeed documented a positive relation between the increasing international capital flows due to greater integration with world financial markets and the vulnerability to sudden reversals in capital flows. Forbes and Warnock (2012), for instance, found that global factors play an important role in explaining ‘waves’ of international capital flows. The more open and integrated a country is to global financial markets, the deeper are the channels through which reversals in capital flows will impact both the real economy and the financial system – and the more critical the policy response becomes to ensure macroeconomic and financial stability.
Fourth, MICs have suffered many costly crises over recent decades, with large drops in output, persistent credit crunches and sharp increases in unemployment and poverty. Although the exact trigger to these crises can be a wide range of events (including political turmoil, a real-estate crash, a sharp decline in the terms of trade or contagion from other economies), making it hard to predict
3 Our discussion of macroprudential policy is thus focused on the extent to which it interacts with monetary policy. For a more general discussion, including coordination issues between these two policies, see Committee on the Global Financial System (2010), Financial Stability Board (2011), Galati and Moessner (2011) and International Monetary Fund (2011b).
4 See Agénor (2012) for a thorough review of the evidence on, and the challenges posed by, international financial integration.
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their exact timing, they are often preceded by sustained imbalances. Thus, any measure that can help to identify sources of weaknesses, prevent these imbalances from emerging, and minimize the chances of a crisis occurring may have large welfare benefits.
The remainder of this paper proceeds as follows. Section II considers the case against using monetary policy to react directly to financial instability; from our perspective, this is tantamount to arguing that macroprudential tools, possibly supplemented by capital controls, are enough, or more than enough to mitigate systemic risk. Section III considers the case for a more proactive monetary policy in response to perceived risks to financial stability, above and beyond the conventional objectives of price and output stability. Section IV discusses what monetary policy should react to, assuming indeed that a more proactive role is desirable. Section V addresses the issue of whether monetary policy should be combined with macroprudential regulation (and possibly capital controls) using a rule-based approach. The last section offers some concluding remarks.
II. The Case Against a More Proactive Role for Monetary Policy
There are a number of arguments that militate against using monetary policy to directly address financial stability concerns.
The first is the so-called Tinbergen principle, which states that to attain a given number of independent policy objectives, there must be at least an equal number of instruments.5 For the issue at hand, with macroeconomic stability and financial stability being the two objectives, this means that two separate tools are needed – the policy interest rate and a macroprudential tool. Put dif- ferently, policy makers necessarily need a tool other than the interest rate – particularly if there are potential trade-offs between policy objectives. With an additional instrument, and in a deterministic environment, the central bank can achieve exactly, and continuously (through dynamic rules) its targets; the two instruments are necessarily complements. From this perspective, the issue of whether monetary policy should respond to financial stability concerns is simply not relevant; it must be combined with macroprudential policy, regardless. This is, implicitly at least, the argument put forward by Svensson (2010). In prac- tice, however, central banks operate in a stochastic world and aim to minimize deviations from their targets rather than achieving them exactly and continu- ously; and because each instrument, manipulated independently, may affect both
5Tinbergen’s principle is concerned with the existence and location of a solution to the system; it does not assert that any given set of policy responses will, in fact, lead to that solution. To assert this, it is necessary to investigate the stability properties of a dynamic system.
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targets in the same direction (thereby reducing volatility in both cases), they may be substitutes. This issue is discussed further in Section IV.
The second argument is that, to the extent that it affects all lending activities (regardless of whether they represent a risk to stability), the policy interest rate is too blunt an instrument to be useful in addressing financial stability concerns, which often have a sectoral dimension – such as, for instance, overheating of the housing market. From that perspective, imposing a cost on the entire economy is not warranted – even though there is evidence to suggest a high correlation between credit expansion, which depends on the cost of borrowing and thus the policy rate, and house price inflation (see Glindro et al. 2008; Goodhart and Hoffman 2008; Claessens et al. 2011). Because the effect of higher policy rates on bank risk taking may depend on each institution’s initial capital position, the net aggregate effect may be limited. Banks with a low capital base (or less to lose), for instance, may try to ‘gamble’ by expanding the asset side of their balance sheets, by lending to increasingly riskier borrowers, whereas highly capitalized banks may choose to diversify their portfolios towards less risky assets. In addition, trying to ‘prick’ a developing housing price bubble through a (possibly very large) economy-wide increase in the cost of borrowing could have an immediate adverse effect on the supply side, given the importance (as indicated earlier) of bank credit in financing working capital needs. In turn, this may increase macroeconomic volatility. Under such conditions, sectoral prudential tools (such as changes in loan-to-value ratios, debt-to-income ratios, countercyclical capital requirements for real-estate lenders, and so on) may be more appropriate to prevent risk concentration.6
The third argument goes even further – depending on the nature of shocks, monetary policy may need to be conducted with caution, because of potentially undesirable side effects. This is what occurs when a country is confronted with a sudden flood of private capital, that is, large inflows induced by changes in external market conditions (Agénor et al. 2012). Indeed, sudden floods have on numerous occasions been a source of macroeconomic instability in many MICs, having led to rapid credit and monetary expansion (due to the difficulty and cost of pursuing sterilization policies), asset price pressures, real exchange rate appreciation and widening current account deficits. This occurred in the aftermath of the surge in capital flows to MICs during 2008–09 and in previous episodes.7 At the same time, the scope for responding to the risk of macroeconomic and financial instability through monetary policy is limited because higher domestic interest
6 However, it is important to recognize at the same time that targeted tools, although they may be less costly than an economy-wide increase in interest rates, could be easier to circumvent than broader measures.
7 See Jongwanich (2010) and Furceri et al. (2011) for instance.
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rates vis-à-vis interest rates in advanced economies may simply exacerbate the flood of private capital. Put differently, monetary policy loses its effectiveness and other instruments (macroprudential tools, capital controls) must be used to manage capital flows and mitigate their destabilizing effects on the domestic economy.
A fourth and related argument is that strengthening macroprudential rules, using both ‘old’ instruments (such as liquidity or leverage ratios, loan-to-value and debt-to-income ratios and so on) and ‘new’ tools, such as countercyclical capital buffers linked to a measure of excessive credit expansion (as envisaged un- der Basel III) and dynamic provisioning, offers a better alternative to monetary policy. In fact, both types of instruments have been used in MICs for years. The Central Bank of Brazil introduced a capital charge in 2000, through a mechanism that links the deviation of credit growth relative to GDP growth. More recently, dynamic provisioning rules have been introduced in several Latin American countries (see Wezel 2010). In addition to reducing balance sheet vulnerabili- ties, these instruments have helped to reduce risk taking and strengthened the financial sector (at least in the case of dynamic provisions), explaining in part why MICs were able to weather the recent global financial crisis with limited strain. As documented by Montoro and Moreno (2011), for instance, reserve requirements were used in Latin America in a countercyclical fashion to smooth the expansion phase of the cycle and to tighten monetary conditions without attracting capital inflows. During the global financial crisis, reserve requirements were lowered, in order to inject liquidity rapidly in local and foreign currency, and restore market activity affected by sudden reversals in capital inflows.8 In another study on Latin America, Terrier et al. (2011) provided a broader review of microprudential policy tools used or available to policy makers in the region to mitigate the procyclical effects of financial cycles. They concluded that, although mainly microprudential in nature, when appropriately calibrated and used in combination over the financial cycle these tools may prove effective for macro- prudential purposes and could contribute significantly to addressing systemic risk.
A fifth argument is that if financial imbalances are related to excessive credit growth, and if credit expansion is fuelled by capital inflows (as is often the case in MICs), then a more effective policy could be to complement macroprudential tools – at least temporarily – with capital controls. The evidence regarding the effectiveness of capital controls is, at best, mixed. In the 1990s, capital controls were only temporarily able to drive a wedge between foreign and domestic interest rates and to reduce pressures on the exchange rate in countries such as Brazil, Chile, Colombia, Malaysia and Thailand (Ariyoshi et al. 2000). More
8Some countries in the region (namely, Brazil and Colombia) also resorted to capital controls.
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recent reviews, which include the Committee on the Global Financial System (2010), Agénor (2012), Habermeier et al. (2011) and the International Monetary Fund (2011a), reached similar conclusions: capital controls appear to have had little effect on overall capital flows, although they may have had some success in altering the composition of these flows.9 In most cases, controls have not been successful at mitigating currency appreciation. Specific econometric estimates on the effectiveness of capital controls covering four MICs during the 2000s (Brazil, Colombia, Korea and Thailand) confirm that controls have met with mixed success. It also appears that the effectiveness of any given measure decays over time. Nevertheless, temporary effectiveness may well be all that policy makers need when faced with sudden floods and neither monetary policy nor macroprudential policy can respond quickly.
A sixth argument is that if the central bank lacks credibility, adding a financial stability objective to monetary policy may confuse markets, weaken perceived commitment to price stability and destabilize expectations – thereby making it more difficult to maintain low inflation. In such conditions, there may be a stabilization cost associated with using monetary policy in a proactive manner. Suppose for instance that policy makers are faced with a negative demand shock that lowers both output and inflation. In an inflation-targeting regime, the correct policy response is to lower the policy rate; there is no trade-off between macroeconomic objectives. But if the central bank is concerned with systemic risk (perhaps because of the belief that low interest rates may promote risk taking motivated by a ‘search for yield’, as discussed later), a conflict between macroeconomic and financial stability objectives emerges: keeping interest rates high means that the risk of deflation must be accepted.
Under such conditions, some observers have proposed as a policy response to lengthen the horizon for achieving the inflation target. This is the same response typically advocated in the case of a (persistent) supply shock, which entails a trade-off between output and inflation. However, concerns about systemic risk, which includes both time and cross-sectional dimensions, may be difficult to convey to agents. Indeed, even though substantial progress has been achieved in recent years, there is still no consensus on defining ‘financial stability’ and how to measure it in its various dimensions. Consequently, lengthening the target horizon may have adverse effects on inflation expectations and central bank credibility. Similar reasoning suggests that allowing instead a wider fluctuation band for the inflation target could have equally adverse effects on credibility.
9 See recent studies by Gochoco-Bautista et al. (2010), McCauley (2008), Habermeier et al. (2011) and Jongwanich et al. (2011).
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III. The Case for a More Proactive Monetary Policy
There are also a number of arguments that militate in favour of making monetary policy more directly responsive to a financial stability objective.
The first argument is that monetary policy, precisely when it is successful at maintaining low and stable prices, may itself induce boom–bust cycles in asset prices; low interest rates may encourage increased risk taking, excessive leverage and promote a ‘search for yield’.10 If so, then there may be a trade-off between macroeconomic and financial stability. This argument has been used in part to highlight a contributing factor to the recent financial crisis: the low interest rates and low inflation that have been associated with the Great Moderation created in advanced economies an environment encouraging increased risk taking – with a switch from lower yielding safe assets into higher yielding risky assets, driving their prices up in the process – and more leveraging, which subsequently led to asset price bubbles. Bean et al. (2010) and Ahrend (2010) found indeed that, during periods when short-term interest rates have been persistently and significantly below what Taylor rules would prescribe, monetary policy has had a significant effect on increases in asset prices, especially housing prices.11
However, the fact that an accommodative policy stance may have an impact on asset prices and credit growth does not mean that monetary policy should respond directly to these variables: if increases in asset prices and credit expansion are expected to lead to an expansion in aggregate demand (through wealth and direct effects on private spending), a policy that reacts to the output gap and (expected) inflation would naturally lead to an endogenous policy response. There would be no need to respond directly to these variables. Put differently, excessive asset prices and credit growth matter only to the extent that they affect the future path of output and inflation. And to the extent that there are trade-offs between (future) financial (in)stability and present macroeconomic stability, they should be addressed through more targeted macroprudential measures, rather than tighter monetary policy.
It is also important to note that there is no evidence that (loose) monetary policy has been a systematic cause of boom–bust cycles in credit and asset prices in MICs. To begin with, very few MICs maintained policy interest rates at low levels for extended periods, so identifying periods during which the correlation
10See Rajan (2005) for the ‘search for yield’ argument. Bean et al. (2010) provide a brief review of the alternative channels through which loose monetary policy may encourage increased risk taking. Gambacorta (2009) provides evidence on the risk channel for industrial countries.
11See, however, Bernanke (2010) for an alternative view in the case of the United States. Svensson (2010) also rejects the view that the financial crisis was caused by an excessively accommodative monetary policy stance.
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between low interest rates and risk taking can be studied in large samples is difficult. A more substantive reason for the lack of evidence on this correlation is that banks in these countries have for years maintained capital ratios well above those required by international standards, as documented by Agénor and Pereira da Silva (2010) and Fonseca et al. (2010). In a sense, having more ‘skin in the game’ reduced incentives to gamble and may have prevented a weakening of balance sheets through imprudent lending practices. A third reason is the fact that in many countries sectoral (micro) prudential tools were actively used to mitigate excessive risk taking. In addition, with non-competitive credit markets (a common characteristic of banking in MICs), low policy rates may mean higher bank spreads, higher profits and possibly less risk. Put differently, if there is no evidence that monetary policy has potentially perverse side effects on financial stability, there should be less concern in attributing a financial stability target to it.
In general, excessive risk taking has to do with procyclicality, which is itself driven by optimistic expectations and the tendency by lenders to relax lending standards and underprice risks in good times. It is indeed well documented that bank intermediation is highly procyclical in MICs (see Claessens et al. 2011; Calderón and Fuentes 2011). Under such conditions, monetary policy – possibly in combination with some specific macroprudential tools – could help to mitigate procyclicality and thereby address the time dimension of systemic risk, through its effect on the economy-wide cost of borrowing.
A second and related argument is that while monetary policy should not be used to ‘prick’ stock market bubbles, it could be quite effective at deflating debt- financed bubbles, especially if they are credit-financed – a common scenario in MICs.12 By inducing a direct and across-the-board increase in the cost of borrowing, monetary policy may be more powerful than macroprudential policy in these circumstances.
A third argument is that it is not obvious that macroprudential policy was all that successful prior to the crisis. Indeed, in several MICs macroprudential measures did not prevent rapid credit growth in the lead-up to the crisis. Prior to the onset of the global financial crisis, credit growth was accelerating in many countries in Latin America, including Brazil, Colombia, Peru and Venezuela.13
A good question is whether these countries would have faced a crisis, even
12 Blinder (2010) and Mishkin (2011) have both emphasized the distinction between credit- fuelled bubbles (such as house price bubbles) and equity-type bubbles (in which credit plays only a minor role) in their analysis of post-crisis monetary policy. However, they are fairly agnostic as to whether the central bank should try to limit credit-based bubbles through regulatory instruments or interest rates.
13 See for instance the April 2011 issue of the IMF’s World Economic Outlook, pp. 5, 76–9.
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without turmoil in advanced economies; if history is any guide, the likelihood appears to be quite high. But rather than an argument in favour of greater reliance on monetary policy, this evidence may be construed as a call for using macroprudential tools more aggressively or for adding new tools to the arsenal of policy makers. Indeed, Colombia (between July 2007 and July 2008) and Peru (in November 2008) both introduced dynamic loan provisioning systems in the aftermath of the global financial crisis. At the same time, the less effective macroprudential tools are, the greater the potential role of monetary policy in contributing to the maintenance of financial stability.
A fourth argument is that macroprudential policy is more subject to lobbying and political pressure than monetary policy. A case in point is the worldwide reaction of the financial sector to the proposed new Basel rules for higher capital requirements, even though research (for the United States and other countries) shows that this policy is likely to lead to only a modest increase in the cost of credit.14
A fifth argument is that too much reliance on macroprudential policy, to the extent that it limits bank credit availability or leads to higher borrowing costs, may foster financial disintermediation by promoting the development of shadow banking and the informal sector – making it in turn difficult to maintain financial stability. From this perspective, the scope and bluntness of the policy rate could be an advantage over macroprudential measures, as it is more difficult to circumvent a general increase in borrowing costs induced by a monetary policy contraction.
A sixth argument is that some of the ‘new’ macroprudential tools envisaged in Basel III are largely untested. There is no clear consensus yet on what tools will work and there is very little evidence on their effectiveness. For instance, regarding the performance of dynamic loan provisioning systems, much of the evidence relates to the Spanish case (see Saurina 2009); yet the conclusion from most studies is that even though these systems may succeed in making banks more resilient, they appear to have limited effectiveness when it comes to re- straining credit expansion.15 Similarly, the introduction of countercyclical capi- tal buffers (just like other macroprudential tools) may create serious operational and institutional challenges, especially in countries where the supervisory envi- ronment is weak to begin with – as is the case in many MICs. It is also not clear what variables they should be related to during the buildup and release phases.
14See Admati et al. (2011) for the impact of capital requirements on the cost of equity and Igan and Mishra (2011) for a discussion of the connection between financial lobbying and financial legislation in the lead-up to the US financial crisis.
15As noted earlier, several countries in Latin America have introduced dynamic loan provisioning systems in recent years, but the experience is too recent to provide new insights.
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Interactions among macroprudential tools are also not well understood; a case in point is the interaction between bank capital requirements and dynamic loan provisioning systems.16 Finally, and quite importantly, some macroprudential tools may alter the way the monetary transmission mechanism operates (see Agénor and Pereira da Silva 2011). What this all means is that there is a good case, if only for a transitory period (during which a better understanding of these issues can be acquired), to rely more on monetary policy to respond to financial stability concerns.
A seventh argument is that both macroeconomic instability and financial instability tend to increase in the lead-up to financial crises.17 This creates a case for monetary policy to react promptly, in normal times, to indications of growing financial vulnerability. By ‘leaning against the financial cycle’, a more active monetary policy may help to stabilize conventional targets (output and inflation). In that case then there could be a stabilization dividend. Indeed, a stable and sound financial system can contribute to macroeconomic stability by facilitating the transmission of monetary policy actions and cushioning the impact of macroeconomic shocks through the financial sector. In addition, a stable and sound financial system may decrease the incidence of financial stress and lead to less disruption in economic activity, which in turn contributes to price stability.
A final argument is that the view, according to which adding a financial stability objective may adversely affect central bank credibility, depends in part on initial conditions. If, for instance, inflation is initially above target, a rise in the policy rate motivated by systemic risk concerns may actually be beneficial. What the ‘credibility problem’ means is that there are new challenges for central banks in terms of transparency and communication of its policy decisions, and the indicators upon which they are based, but these are not insurmountable. After all, when some central banks in MICs initially adopted a measure of ‘core’ inflation, as opposed to headline inflation, as their measure of price stability, they faced significant problems in conveying to the public the nature of their objective, and the reasons for making their particular choice; over time, with communication improving, these issues became better understood. There is no reason to believe
16 The common view is that bank capital should cover for unexpected credit losses, whereas dynamic loan loss provisions are intended to cover expected credit losses. However, introducing either one of those regulatory regimes while the other is present may change the behaviour of banks and thus the effectiveness of both types of tools. This may occur, for instance, if the reasons why banks hold (excess) capital buffers are altered by the introduction of loan loss provisions, and if capital buffers have a signalling effect that translates into changes in their market borrowing costs.
17 See Demirguc-Kunt and Detragiache (2005) for a review of the evidence for developing countries.
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that the same may not occur with a financial stability target – even though, as noted earlier, there is no consensus yet on how to measure financial stability. A good point of departure would therefore be to begin with a definition of financial stability as a final target. Because the concept has proved elusive, this is not a simple task; a sensible strategy perhaps is to follow an operational approach and respond to an intermediate financial target, as discussed in the next section.
IV. What Should Monetary Policy React to?
Assuming that the balance of arguments is in favour of a more proactive role for monetary policy – if only for a transitory period, as noted earlier – in addressing financial stability concerns, what should central banks react to? Many MICs have adopted a flexible inflation-targeting regime in recent years, with much success prior to the crisis. In these regimes, the optimal interest rate policy is a Taylor-type rule, which involves linking the policy interest rate to current or expected inflation and the output gap.18
Our view is that in the context of MICs, there is much merit in augmenting the interest rate rule by adding a measure of the private-sector credit gap, defined either in terms of growth rates (as the difference between the actual growth rate of that variable and a ‘reference’ growth rate), or in terms of deviations of the credit-to-GDP ratio with respect to a reference ratio. This would allow monetary policy (which can address only the time dimension of systemic risk, as noted earlier) to help to counter accelerator mechanisms that inflate credit expansion and asset prices, which are common manifestations of financial imbalances. In particular, rapid credit expansion tends to go hand-in-hand with a deterioration in lending origination standards and credit quality (see Dell’Ariccia and Mar- quez 2006). During upturns, credit standards tend to be more lenient, both in terms of screening of borrowers and in collateral requirements. As a result, a greater number of riskier borrowers are able to secure bank loans, whereas the share of collateralized loans tends to decrease. During boom times, the adverse selection problems created by informational asymmetries between lenders and borrowers are therefore magnified. In turn, the weakening of lending standards may increase vulnerability to financial distress when the economy experiences a downturn.
In addition, although credit and asset price cycles often exacerbate each other, several studies have found that credit is also a useful leading indicator of asset price busts; by contrast, there is no strong evidence that asset prices (in particular,
18See Svensson (1997) for a formal analysis. Taylor rules, sometimes augmented with an exchange rate pressure variable, appear to perform fairly well in practice for some MICs; see for instance de Mello and Moccero (2011) for Latin America.
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equity prices) are good out-of-sample predictors. More generally, rapid credit expansion – often associated with episodes of large capital inflows in MICs, as documented earlier – is often a warning sign of financial instability; even though not all episodes of credit booms end up in crises, almost invariably crises are preceded by episodes of credit booms. There is indeed robust evidence that credit booms significantly raise the likelihood of an asset price bust or a financial crisis in MICs.19 Recessions whose origin is the collapse of credit- fuelled bubbles – periods during which banks make loans that appear to have abnormally low expected returns – also tend to be more severe and longer lasting than those generated by ‘normal’ monetary policy contractions aimed at curbing inflationary pressures.
A third consideration is that most MICs do not have reliable data on land and property prices, and equity prices tend to be highly volatile. By contrast, credit data are readily available and usually subject to only small revisions (if at all) over time. In practice, many central banks in MICs are already paying much attention to credit growth – undoubtedly because of the importance of banks in the financial system, as discussed earlier.
Another important argument for responding to a credit growth gap is that this could be desirable not only for macroprudential reasons, but also because of the unreliability of real-time (preliminary) output gap measures in MICs. Differences in output gap measures based on real-time and final real GDP estimates can be quite substantial, as shown by Cusinato et al. (2010) for Brazil, with errors going in both directions. Similar results have been obtained for other countries. In the presence of large errors in the measurement of output gaps, it may in fact be optimal to reduce the weight attached to the output gap in a ‘real-time’ Taylor-type policy rule. At the same time, if the credit gap is closely related to final estimated output, the weight of that variable should be increased.
In a sense, the credit gap can be viewed as an intermediate target, concerns about which are easier to convey than those about a multi-faceted and hard- to-define final target, financial stability. In this approach, there is therefore an asymmetry in defining the central bank’s policy loss function, because infla- tion and output are final targets. Because of the difficulty of defining finan- cial stability as a final target (at least in the current state of affairs), using an intermediate target that is easier to identify may facilitate communication with the public and alleviate, to some extent, the credibility issues mentioned earlier.
19 See International Monetary Fund (2009), Claessens et al. (2011) and Calderón and Fuentes (2011). Gerdesmeier et al. (2010) found that credit aggregates also play a significant role in predicting asset price busts in industrial countries.
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The practical implementation of this ‘augmented’ policy rule needs of course to be thought out carefully. A first issue is whether the central bank should consider a real or a nominal credit gap (if it is measured in terms of growth rates), and whether it should consider a broad measure of aggregate credit or only a component of total credit. As noted earlier, working capital loans are related to changes in the supply side, not the demand side, of the economy; if the credit gap is to be used in part as a substitute to the output gap as a measure of excess aggregate demand, it might be argued that these loans should be excluded from the measure to which the central bank should respond to. However, it may also be argued that working capital loans are substitutes for firms’ internal resources (or cash flows), which can now be used to finance longer term investment – thereby indirectly affecting aggregate demand. This would militate in favour of using a broad aggregate. Fungibility and evergreening problems are also important considerations in choosing between narrow and broad credit aggregates.
A second issue is whether the ‘reference’ growth rate or credit ratio should be calculated as a trend (as proposed for instance in the calculation of the counter- cyclical capital buffer under Basel III) or rather on the basis of an equilibrium value that is related to some fundamental determinants, such as population growth, urbanization and so on. This second approach may be more appro- priate for MICs, because it would help to account for financial inclusion – an important consideration for many countries where the scope of the formal finan- cial system, and access to credit and other financial services, are limited to begin with. The implicit view here is that financial inclusion, by reducing reliance on the unregulated financial system, and increasing opportunities for risk sharing and consumption smoothing, helps to promote financial stability in the longer run (see Hawkins 2006).
At the same time, it is important to keep in mind that the credit gap is still a noisy indicator; false signals are inevitable and may raise the risk of policy errors. A policy response should be contingent on the magnitude of the credit gap, that is, it should occur only if the gap exceeds a certain threshold. In so doing, the primacy of the macroeconomic stability objective in ‘normal times’ would be maintained and credibility problems mitigated.
Yet, during episodes of sudden floods induced by external shocks, raising policy interest rates to account for excessive credit expansion may exacerbate the problem by triggering more inflows, as discussed earlier. Both points are arguments for combining (an augmented) monetary policy rule with macro- prudential tools. Indeed, given that monetary policy cannot address the cross- section dimension of systemic risk (that is, how risk is distributed within the financial system at a point in time), a combination of these two policies may be inescapable.
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Macroeconomic Stability, Financial Stability, and Monetary Policy Rules 219
V. How Should Macroprudential Regulation and Monetary Policy Be Combined?
An important practical issue for central banks is how an augmented monetary policy rule (of the type discussed earlier) and macroprudential rules should be combined. To address it requires understanding how the two policies interact. As noted earlier, even though the Tinbergen principle implies that in a deterministic world the two policies are complements if the two objectives (macroeconomic stability, financial stability) are to be achieved exactly, they may be substitutes if the central bank’s goal (in a stochastic environment) is to minimize deviations from targets over time, rather than achieve them exactly and continuously. This would occur if each instrument affects both targets in the same direction (lower volatility); due to decreasing marginal returns to each instrument, they may reinforce each other. It is therefore important to study jointly augmented monetary policy rules and macroprudential rules to understand how they should be combined.
Studies along these lines for MICs include those of Agénor et al. (2011, 2012), which focus on a Basel III type countercyclical regulatory rule and a monetary policy rule augmented with a credit gap variable (measured in terms of deviations of the growth rate of loans for investment from its steady- state value). Thus, the central bank sets its policy instrument in part to ‘lean against financial winds’ in a systematic fashion. Capital adequacy requirements are decomposed into a deterministic (minimum) requirement and a cyclical component related again to deviations in the growth rate of credit for invest- ment from its steady-state value. Macroeconomic stability is defined in terms of the volatility of a combination of the output gap and inflation, whereas fi- nancial stability is defined in terms of the volatility of a composite indicator that includes real house prices, bank loan spreads and the credit-to-GDP ratio. A composite index of economic stability is also defined, under the assump- tion that the central bank (still) attaches more importance to macroeconomic stability.
In response to a positive housing demand shock (meant to capture a housing boom) or a sudden flood (large capital inflows induced by external shocks), the analysis shows that the two instruments are complementary rather than substitutes; even with an aggressive interest rate response to inflation and credit gaps, it is optimal to also rely on the countercyclical regulatory rule under most circumstances. This complementarity is particularly important dur- ing episodes of sudden floods where, as indicated earlier, the central bank has limited ability to respond to inflationary pressures by raising interest rates.
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VI. Concluding Remarks
A key issue on the agenda of policy makers, in industrial and middle-income developing countries alike, relates to the roles of monetary policy and macro- prudential rules in mitigating procyclicality and promoting macroeconomic and financial stability. In this paper, we focused the discussion on the arguments for and against attributing an explicit financial stability objective to monetary policy – as a complement, or substitute, to macroprudential policy. This dis- cussion was conducted from the perspective of MICs, where banks continue to dominate the financial system and bank credit plays a critical role both on the supply and demand sides. We also discussed, assuming that a more proac- tive role is desirable, what monetary policy should react to, and to what extent it should be combined with macroprudential regulation and possibly capital controls.
The findings in this paper bear on the broader debate, sparked by the global financial crisis, about the role of monetary policy and macroprudential regu- lation – viewed independently and jointly – in achieving macroeconomic and financial stability in both industrial and developing countries. Our review of the various arguments that have been put forward indicates that, on balance, there may be a good case for monetary policy in MICs to be more proactive and address the time dimension of systemic risk – if only during a transitory period, as more is learnt about the implementation and performance of the new macroprudential rules that are currently being discussed, as part of the Basel III agreement and in other policy circles. In particular, there are robust arguments in favour of monetary policy in MICs reacting to a measure of the private-sector credit gap because of concerns about financial stability. The credit gap acts as an intermediate target, which is relatively easy to calculate (given a reference growth rate or credit-to-GDP ratio) and easier to explain to the public than the more elusive final target of financial stability. By making the policy response contingent on the magnitude of the credit gap itself, the primacy of the macroeconomic stability target in ‘normal’ times would be maintained and credibility problems mitigated. Another important argument for responding to the credit gap is the high degree of uncertainty in these countries about real-time estimates of the output gap.
Nevertheless, our analysis also implies that there is no escape from the fact that monetary policy in MICs needs to be combined with macroprudential regu- lation – because monetary policy cannot, in any event, address the cross-section dimension of systemic risk, and because these countries often face circumstances (such as sudden surges in capital flows) where interest rate policy may have unde- sirable side effects that may be detrimental to both macroeconomic and financial stability.
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Macroeconomic Stability, Financial Stability, and Monetary Policy Rules 221
Pierre-Richard Agénor School of Social Sciences Oxford Road University of Manchester Manchester M13 9PL UK [email protected]
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Macroprudential-and-monetary-policies-Implications-for-financial-stability-and-welfare_2014_Journal-of-Banking-Finance.pdf
Journal of Banking & Finance 49 (2014) 326–336
Contents lists available at ScienceDirect
Journal of Banking & Finance
j o u r n a l h o m e p a g e : w w w . e l s e v i e r . c o m / l o c a t e / j b f
Macroprudential and monetary policies: Implications for financial stability and welfare
http://dx.doi.org/10.1016/j.jbankfin.2014.02.012 0378-4266/� 2014 Elsevier B.V. All rights reserved.
⇑ Corresponding author. Tel.: +44 (0)1159514768. E-mail addresses: [email protected] (M. Rubio), jose.carrasco@
urjc.es (J.A. Carrasco-Gallego). 1 See, for instance, Abraham et al. (2008) and Duca et al. (2011).
Margarita Rubio a,⇑, José A. Carrasco-Gallego a,b a University of Nottingham, School of Economics, University Park, Nottingham NG7 2RD, UK b Departamento de Economía Aplicada I, Universidad Rey Juan Carlos, P. de los Artilleros, 28032 Madrid, Spain
a r t i c l e i n f o
Article history: Received 15 July 2013 Accepted 16 February 2014 Available online 6 March 2014
JEL classification: E32 E44 E58
Keywords: Macroprudential Monetary policy Welfare Financial stability Loan-to-value Kaldor–Hicks efficiency
a b s t r a c t
In this paper, we analyze the implications of macroprudential and monetary policies for business cycles, welfare, and financial stability. We consider a dynamic stochastic general equilibrium (DSGE) model with housing and collateral constraints. A macroprudential rule for the loan-to-value ratio (LTV), which responds to credit growth, interacts with a traditional Taylor rule for monetary policy. We compute the optimal parameters of these rules both when monetary and macroprudential policies act in a coor- dinated and in a non-coordinated way. We find that both policies acting together unambiguously improves the stability of the system. In both cases, this interaction is welfare improving for the society, especially in the case of the non-coordinated game. There is though a trade-off between borrowers and savers. However, borrowers can compensate the saver’s welfare loss �a la Kaldor–Hicks to achieve a Par- eto-superior outcome.
� 2014 Elsevier B.V. All rights reserved.
‘‘Normally, however, the policy rate is not the only available tool, and much better instruments are available for achieving and main- taining financial stability. Monetary policy should be the last line of defence of financial stability, not the first line.’’ Svensson (2012)
1. Introduction
The housing sector is key to understand how the recent finan- cial crisis developed and, therefore, crucial for designing recovery and prevention policies. The financial crisis was born in the hous- ing sector, grew in the financial sector and had its final conse- quences in the real sector. Financial innovations made the financial system increasingly complex and interconnected, leading to an expansion of systemic risk, especially through the mortgage market. In this context, when house prices collapsed, micro-pru- dential policies, those dedicated to prevent the risk from each com-
pany, had not managed to avoid the contagion to the real sector, and the crisis spread across the financial system to the real econ- omy. Then, a great recession affected the whole economy, causing a high level of unemployment. Thus, from a policy perspective, tra- ditional measures have not seemed to be sufficient to, first, avoid the crisis and, second, have a fast and effective recovery.
As a result, several institutions have implemented macropru- dential tools in order to explicitly promote the stability of the financial system in a global sense, not just focusing on individual companies. The goal of this kind of regulation is to avoid the trans- mission of financial shocks to the broader economy. Some exam- ples of macroprudential tools are asset-side tools (loan-to-value (LTV) and debt-to-income ratio caps), liquidity-based tools (coun- tercyclical liquidity requirements), or capital-based tools (counter- cyclical capital buffers, sectorial capital requirements or dynamic provisions).
The LTV requirement is a limit on the value of a loan relative to the underlying collateral (e.g. residential property). Several studies have pointed out that higher LTV ratios combined with higher risk mortgages contributed to the mortgage crisis.1 The LTV is nowa-
M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336 327
days described as one of the main macroprudential instruments to ‘‘mitigate and prevent excessive credit growth and leverage’’ by the European Systemic Risk Board.2 Within the EU, LTV limits are available in the national prudential framework of 16 Member States.3
The aim of this paper is to evaluate the implications of a macro- prudential LTV tool for business cycles, financial stability, and wel- fare, as well as its interaction with monetary policy. In order to do that, we use a dynamic stochastic general equilibrium (DSGE) model which features a housing market.
The modelling framework consists of an economy composed of borrowers and savers. In particular, our model imposes a limit on borrowing, that is, loans need to be collateralized by a proportion of the value of the assets that the borrower owns. This proportion can be interpreted as an LTV. The macroprudential tool we propose is a rule that automatically reduces loan-to-values when there is a credit boom, therefore limiting the expansion of credit. We assume that there exists a macroprudential Taylor-type rule for the LTV ra- tio, so that it responds to credit growth, in the spirit of the Basel III regulation which aims at avoiding episodes of excessive credit growth. The monetary policy literature has extensively shown that simple rules result in a good performance; therefore, it seems sen- sible to apply these kinds of rules to macroprudential supervision. This microfounded general equilibrium model allows us to explore all the interrelations that appear between the real economy and the credit market. Furthermore, such a model can deal with wel- fare-related issues.
In the context of this model, we address several research ques- tions. First, we study the welfare gain for each agent and for the aggregate both for different levels of a static LTV and for different values of the reaction parameters of the macroprudential rule. In this way, we discuss the welfare trade-offs that may appear be- tween borrowers and savers. Second, we analyze the combination of monetary and macroprudential policy parameters that maxi- mize welfare when the macroprudential regulator and the central bank are coordinated and when they are not. Third, we discuss a Pareto-superior outcome to overcome this trade-off by a system of transfers �a la Kaldor–Hicks. Then, we study the dynamics of the model under the optimal parameters. Finally, we graphically convey our results to highlight the effects on macroeconomic and financial stability of introducing a new macroprudential policy based on the LTV ratio.
The rest of the paper continues as follows: Section 1.1 reviews the literature. Section 2 describes the model. Section 3 presents the welfare analysis. Section 4 computes the optimal parameter combination of the different policies in a coordinated and in a non-coordinated situation. It also develops a rule to obtain a Pare- to-superior outcome, presents results from simulations, and con- veys the results graphically to show the effects of the macroprudential policy on financial and macroeconomic stability. Section 5 concludes.
1.1. Related literature
Our paper fits into the literature that introduces a macropru- dential rule and studies its effects using a DSGE model. Other examples are, for instance, Antipa et al. (2010), who uses a DSGE model to show that macroprudential policies would have been effective in smoothing the past credit cycle and in reducing the intensity of the recession. Another example is Borio and Shim (2007), which emphasizes the complementary role of macropru- dential policy to monetary policy and its supportive function as a
2 See Recommendation of the European Systemic Risk Board (2013). 3 More world results are available in Lim et al. (2011).
4 Borio et al. (2001) also evaluated limits on the LTV. 5 See Borio and Shim (2007) for a distinction between rules and discretion in
calibrating the tools of macroprudential policy. 6 See Galati and Moessner (2013) for an extensive review.
built-in stabilizer. As well, N’Diaye (2009) shows that monetary policy can be supported by countercyclical prudential regulation. Angelini et al. (2012) uses a DSGE model with a banking sector and shows interactions between capital requirement ratios as a macroprudential tool and monetary policy; they find that macro- prudential policies are most helpful to counter financial shocks that lead the credit and asset price booms. We find in our paper that macroprudential policies moderate credit booms. Further- more, for housing demand shocks, the combination of the macro- prudential and the monetary policies manages to control credit without moderating the real effects of the boom.
Since there is an extensive consensus that the origin of the last crisis is related to real estate booms and busts, we have focused on the effects of a macroprudential tool that has to do with the hous- ing sector. However, while most papers in the field tend to analyze macroprudential policies through the lens of a countercyclical bank leverage rule (e.g. Angelini et al., 2012; Christensen et al, 2011), in our paper, we study how a key element of the real estate sector, namely the LTV, can serve as a macroprudential tool to im- prove financial stability.4 With a macroprudential orientation, Kan- nan et al. (2012) also examines a monetary policy rule that reacts to prices, output and changes in collateral values with a macropruden- tial instrument based on the LTV; they remark on the importance of identifying the source of the shock of the housing price boom when assessing policy optimality. Funke and Paetz (2012) considerers a non-linear version of a macroprudential rule for the LTV. Following this literature, we propose a macroprudential policy based on a Tay- lor-type automatic rule.5 By analogy with monetary policy, rule- based macroprudential tools – for example, automatic stabilizers – appear appealing (Goodhart, 2004).
One question that arises from the topic is what the objective of the macroprudential authority should be. In recent years, research on macroprudential issues has been wide and intense6 and there is an increasing consensus among academics and policy makers that ‘‘the ultimate objective of macroprudential policy is to contribute to the safeguard of the stability of the financial system as a whole’’ (Recommendation of the European Systemic Risk Board, 2013). In this way, Almeida et al. (2006) has studied the effect on the ampli- tude of the credit cycle results from the mitigating impact of more stringent LTV ratios on the ‘financial accelerator’ mechanism. They find that when a positive income shock leads to an increase in hous- ing prices, the increase in borrowing is expected to be lower in coun- tries with lower LTV ratios. Gelain et al. (2013) evaluates different policy actions that might be used to dampen the resulting excess volatility, including a direct response to house-price growth or credit growth in the central bank’s interest rate rule, the imposition of a more restrictive loan-to-value ratio, and the use of a modified collat- eral constraint that takes into account the borrower’s wage income. We contribute to this line of research, finding that when we use the macroprudential policy based on the LTV, both the macroeconomy and the financial system become more stable. To illustrate that, we construct policy frontiers (Taylor curves) including not only the tra- ditional objectives of monetary policy but also the objective of the macroprudential regulator: financial stability. As a measure of finan- cial stability we propose the variability of borrowing. This three- dimensional policy frontier shows graphically that the macropru- dential policy unambiguously helps to achieve a more stable finan- cial and macroeconomic situation.
A central issue that we cover in our paper is the interaction be- tween monetary and macroprudential policies. There is no consen- sus on whether both policies should act in a coordinated or in a
328 M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336
non-coordinated way. For instance, Bean et al. (2010), with a DSGE model adapted from Gertler and Karadi (2011), studies how the use of a macroprudential policy tool based on a lump-sum levy or subsidy on the banking sector might affect the conduct of mon- etary policy. Their results suggest that monetary and macropru- dential policies should be coordinated, since they are not merely substitutes, but they mention that the issue of coordination needs to be studied further. Beau et al. (2012) claims that it is preferable to have a combination of separate objectives for monetary and macroprudential policies, with monetary policy taking the macro- economic effects of macroprudential policy into account in choos- ing interest rates, that is, the non-coordinated case would be preferable. Angelini et al. (2012) studies the coordination issue in a context in which the macroprudential regulator uses capital requirements as a tool to achieve financial stability. They find that lack of cooperation between a macroprudential authority and a central bank may actually generate conflicting policies and, there- fore, cooperation is preferred. In our paper, we also distinguish be- tween the cases of coordination and non-coordination to try to shed some light on this issue. As argued by Svensson (2012), we find that the non-coordination game delivers higher social welfare and then is preferable. When each authority focuses on its own objective, they are more effective in minimizing both macroeco- nomic and financial variability.
Finally, measuring the potential welfare improvement of mac- roprudential policies has deserved the special attention of academ- ics. Some papers have found that the macroprudential reaction to exogenous shocks can make some people better off (typically bor- rowers), but not every type of household, or not in all cases. For in- stance, Lambertini et al. (2013) extends the Iacoviello and Neri (2010) model to incorporate news shocks and a macroprudential rule on the LTV. They find that an optimized LTV-ratio rule that re- sponds to credit growth is a Pareto-improving policy compared to the use of a constant LTV ratio. Campbell and Hercowitz (2009) performes a welfare analysis in a DSGE model with borrowers and savers and determines that, although high LTV ratios have a di- rect positive effect on welfare through constraint relaxation, other indirect effects may dominate. Angelini et al. (2012) also discusses the issue and concludes that there is no regime that makes all agents better-off. They claim that the optimal (from a welfare per- spective) monetary and macroprudential policies may depend on which agent’s welfare is used as objective in the computation of the policies, and also on the type of shock considered. In our paper, we actively contribute to this discussion. We focus on highlighting the welfare trade-offs between agents in order to carefully charac- terize the conditions under which there is room for Pareto improvements. By analyzing welfare for a static LTV, we find an LTV threshold below which there is room for Pareto-improving solutions. However, for higher values the trade-off between bor- rowers and savers appears. Since a plausible value for the LTV tends to be higher than this value, we also observe this trade-off when calculating the optimal macroprudential rule. Thus, we pro- pose a system of transfers �a la Kaldor–Hicks in which borrowers would compensate savers so that they are indifferent between hav- ing the macroprudential policy or not. In this way, we obtain a Par- eto-superior outcome.7
2. Model setup
The modelling framework is a DSGE model with a housing mar- ket, following Iacoviello (2005). The model is solved by log-linear-
7 This is the first time that this criterion has been applied in the macroprudential context, albeit it is widely used in regulatory analysis in Law and Economics. See for instance Posner (2007).
izing the equilibrium equations around a well-defined steady state. The use of DSGE models for the study of macroprudential policies has some limitations and deserves some discussion. When using DSGE models for monetary policy evaluation, the dynamics of the model are matched with the monetary policy transmission mechanism found in the data. However, for macroprudential poli- cies, empirical applications are rare. Furthermore, the macropru- dential analysis often refers to the vulnerability of the financial system to exceptional events related to non-equilibrium, which cannot be captured by a DSGE model. At the same time, a drawback of DSGE models is that they are infinite horizon models and, there- fore, are not well suited to incorporate state contingency in a meaningful way. As a result, DSGE models have problems of mod- elling financial intermediation and frictions (Bean, 2009). However, regardless of these limitations, DSGE models are often used for macroprudential analysis since they count with other advantages: First, they can be compared with a benchmark in which there is only monetary policy. Second, they include many sources of shocks that can be used to check for different economic trajectories. More- over, they rely on general equilibrium analysis and are suitable for simulations to study the impact of new policy instruments. Also, calibrated parameters can be altered to test for alternative policy scenarios. And finally, since DSGE models are microfounded, they are suitable to study welfare issues.8
In our model, the economy features patient and impatient households, a final goods firm, and a central bank which conducts monetary policy. Households work and consume both consump- tion goods and housing. Patient and impatient households are sav- ers and borrowers, respectively. Borrowers are credit constrained and need collateral to obtain loans. The representative firm con- verts household labor into the final good. The central bank follows a Taylor rule for the setting of interest rates. The macroprudential authority sets the LTV following a Taylor-type rule.
2.1. Savers
Savers maximize their utility function by choosing consump- tion, housing and labor hours:
max Cs;t;Hs;t;Ns;t
E0 X1 t¼0
bts log Cs;t þ jt log Hs;t � ðNs;tÞ
g
g
� � ;
where bs 2 ð0; 1Þ is the patient discount factor, E0 is the expectation operator and Cs;t; Hs;t and Ns;t represent consumption at time t, the housing stock and working hours, respectively. 1=ðg � 1Þ is the la- bor supply elasticity, g > 0. jt represents the weight of housing in the utility function. We assume that log ðjtÞ¼ log ðjÞþ uJt , where uJt follows an autoregressive process. A shock to jt represents a shock to the marginal utility of housing.
Subject to the budget constraint:
Cs;t þ bt þ qtðHs;t � Hs;t�1Þ¼ Rt�1bt�1
pt þ ws;t Ns;t þ Ft; ð1Þ
where bt denotes bank deposits, Rt is the gross return from deposits, qt is the price of housing in units of consumption, and ws;t is the real wage rate. F t are lump-sum profits received from the firms. The first order conditions for this optimization problem are as follows:
1 Cs;t ¼ bs Et
Rt ptþ1 Cs;tþ1
� � ; ð2Þ
wst ¼ðNs;tÞ g�1Cs;t; ð3Þ
jt Hs;t ¼
1 Cs;t
qt � bsEt 1
Cs;tþ1 qtþ1: ð4Þ
8 See Brázdik et al. (2012) for further discussion.
M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336 329
Eq. (2) is the Euler equation, the intertemporal condition for con- sumption. Eq. (4) represents the intertemporal condition for housing, in which, at the margin, benefits for consuming housing equate costs in terms of consumption. Eq. (3) is the labor-supply condition.
2.2. Borrowers
Borrowers solve:
max Cb;t;Hb;t;Nb;t
E0 X1 t¼0
btb log Cb;t þ jt log Hb;t � ðNb;tÞ
g
g
� � ;
where bb 2 ð0; 1Þ is the impatient discount factor, subject to the budget constraint and the collateral constraint:
Cb;t þ Rt�1bt�1
pt þ qtðHb;t � Hb;t�1Þ¼ bt þ W b;t Nb;t; ð5Þ
Et Rt
ptþ1 bt ¼ kt Et qtþ1 Hb;t; ð6Þ
where bt denotes bank loans and Rt is the gross interest rate. kt can be interpreted as a loan-to-value ratio. The borrowing constraint limits borrowing to the present discounted value of their housing holdings. The first order conditions are as follows:
1 Cb;t ¼ bbEt
Rt ptþ1Cb;tþ1
� � þ kt Rt; ð7Þ
wb;t ¼ðNb;tÞ g�1Cb;t; ð8Þ
jt Hb;t ¼
1 Cb;t
qt � bbEt 1
Cb;tþ1 qtþ1
� � � kt kt Etðqtþ1ptþ1Þ; ð9Þ
where kt denotes the multiplier on the borrowing constraint. 9 These
first order conditions can be interpreted analogously to those of savers.
2.3. Firms
2.3.1. Final goods producers There is a continuum of identical final goods producers that
operate under perfect competition and flexible prices. They aggre- gate intermediate goods according to the production function
Y t ¼ Z 1
0 Y tðzÞ
e�1 e dz
� � e e�1
; ð10Þ
where e > 1 is the elasticity of substitution between intermediate goods. The final good firm chooses Y tðzÞ to minimize its costs, resulting in demand of intermediate good z:
Y tðzÞ¼ PtðzÞ
Pt
� ��e Y t: ð11Þ
The price index is then given by:
Pt ¼ Z 1
0 PtðzÞ
1�e dz � � 1
e�1
: ð12Þ
2.3.2. Intermediate goods producers The intermediate goods market is monopolistically competitive.
Following Iacoviello (2005), intermediate goods are produced according to the production function:
Y tðzÞ¼ At Ns;tðzÞ aNb;tðzÞ
ð1�aÞ ; ð13Þ
where a 2 ½0; 1� measures the relative size of each group in terms of labor.10 This Cobb–Douglas production function implies that labor
9 Through simple algebra it can be shown that the Lagrange multiplier is positive in the steady state and thus the collateral constraint holds with equality.
10 Notice that the absolute size of each group is one.
11 It could also be interpreted as the savers being older than the borrowers therefore more experienced.
12 Symmetry across firms allows us to write the demands without the index z. 13 Variables with a hat denote percent deviations from the steady state.
efforts of constrained and unconstrained consumers are not perfect substitutes. This specification is analytically tractable and allows for closed form solutions for the steady state of the model. This assumption can be economically justified by the fact that savers are the managers of the firms and their wage is higher than that of the borrowers.11
At represents technology and it follows the following autore- gressive process:
log ðAtÞ¼ qA log ðAt�1Þþ uAt; ð14Þ
where qA is the autoregressive coefficient and uAt is a normally dis- tributed shock to technology. We normalize the steady-state value of technology to 1.
Labor demand is determined by:
ws;t ¼ 1 Xt
a Y t
Ns;t ; ð15Þ
wb;t ¼ 1 Xt ð1 � aÞ
Y t Nb;t
; ð16Þ
where Xt is the markup, or the inverse of marginal cost. 12
The price-setting problem for the intermediate good producers is a standard Calvo-Yun setting. An intermediate good producer sells its good at price PtðzÞ, and 1 � h;2 ½0; 1�, is the probability of being able to change the sale price in every period. The optimal re- set price P�tðzÞ solves: X1 k¼0 ðhbÞkEt Kt;k
P�tðzÞ Ptþk
� e=ðe � 1Þ
Xtþk
� � Y�tþkðzÞ
� � ¼ 0; ð17Þ
where e=ðe � 1Þ is the steady-state markup. The aggregate price level is then given by:
Pt ¼ hP1�et�1 þð1 � hÞ P � t
� 1�eh i1=ð1�eÞ : ð18Þ
Using (17) and (18), and log-linearizing, we can obtain a stan- dard forward-looking New Keynesian Phillips curve p̂t ¼ bEtp̂tþ1 � wx̂t þ upt , that relates inflation positively to future inflation and negatively to the markup ðw �ð1 � hÞð1 � bhÞ=hÞ. upt is a normally distributed cost-push shock.13
2.4. Monetary policy
We consider a Taylor rule which responds to inflation and out- put growth:
Rt ¼ðRt�1Þ qððptÞ
ð1þ/RpÞðY t=Y t�1Þ /Ry RÞ
1�q eRt; ð19Þ
where 0 6 q � 1 is the parameter associated with interest-rate inertia, /Rp P 0 and /
R y P 0 measure the response of interest rates
to current inflation and output growth, respectively. eRt is a white noise shock with zero mean and variance r2e .
2.5. A macroprudential rule for the LTV
In standard models, the LTV ratio is a fixed parameter which is not affected by economic conditions. However, we can think of reg- ulations of LTV ratios as a way to moderate credit booms. When the LTV ratio is high, the collateral constraint is less tight. And, since the constraint is binding, borrowers will borrow as much as they are allowed to. Lowering the LTV tightens the constraint and therefore restricts the loans that borrowers can obtain. Recent
,
0 0.1 0.2 0.3 0.4 0.5 0.6 0.7 0.8 0.9 1 -1
-0.5
0
0.5
1
1.5
2
2.5
3
3.5
4
LTV
W el
fa re
g ai
n (C
E )
Total Savers Borrowers
Fig. 1. Welfare gains from increasing the LTV ratio, everything else constant. Benchmark case: no macroprudential regulator.
330 M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336
research on macroprudential policies has proposed Taylor-type rules for the LTV ratio so that it reacts inversely to variables such as the growth rates of GDP, credits, the credit-to-GDP ratio or house prices. These rules can be a simple illustration of how a mac- roprudential policy could work in practice. Here, we assume that there exists a macroprudential Taylor-type rule for the LTV ratio, so that it responds to credit growth, in the spirit of the Basel III reg- ulation which aims at avoiding episodes of excessive credit growth14:
kt ¼ kSS bt
bt�1
� ��/k b
; ð20Þ
where kSS is a steady state value for the loan-to-value ratio, and /kb P 0 measures the response of the loan-to-to value to the credit growth. This kind of rule would deliver a lower LTV ratio in booms, when there is excessive credit growth, therefore restricting the credit in the economy and avoiding a credit boom derived from good economic conditions (and symmetrically for recessions).15
2.6. Equilibrium
The market clearing conditions are as follows:
Y t ¼ Cs;t þ Cb;t: ð21Þ
The total supply of housing is fixed and it is normalized to unity:
Hs;t þ Hb;t ¼ 1: ð22Þ
3. Welfare
3.1. Welfare measure
To assess the normative implications of macroprudential and monetary policies, we numerically evaluate the welfare derived in each case. As discussed in Benigno and Woodford (2008), the two approaches that have recently been used for welfare analysis in DSGE models include either characterizing the optimal Ramsey policy, or solving the model using a second-order approximation to the structural equations for given policy and then evaluating welfare using this solution. As in Mendicino and Pescatori (2007), we take this latter approach to be able to evaluate the welfare of the two types of agents separately.16 The individual welfare for sav- ers and borrowers, respectively, as follows:
W s;t � Et X1 m¼0
bms log Cs;tþm þ j log Hs;tþm � ðNs;tþmÞ
g
g
� � ; ð23Þ
W b;t � Et X1 m¼0
bmb log Cb;tþm þ j log Hb;tþm � ðNb;tþmÞ
g
g
� � : ð24Þ
Following Mendicino and Pescatori (2007), we define social welfare as a weighted sum of the individual welfare for the differ- ent types of households:
W t ¼ð1 � bsÞW s;t þð1 � bbÞW b;t: ð25Þ
14 See Kannan et al. (2012) for a similar specification. 15 The feasibility of implementing an LTV rule at a quarterly frequency may be
questionable in practice. However, as the Committee on the Global Financial System (2012) suggests, once the legal and operational infrastructure is in place, LTV changes can be implemented rather rapidly, given that many jurisdictions have ample experience with these tools at the practical level.
16 We used the software Dynare to obtain a solution for the equilibrium implied by a given policy by solving a second-order approximation to the constraints, then evaluating welfare under the policy using this approximate solution, as in Schmitt- Grohe and Uribe (2004). See Monacelli (2006) for an example of the Ramsey approach in a model with heterogeneous consumers.
Each agent’s welfare is weighted by her discount factor, respec- tively, so that all the groups receive the same level of utility from a constant consumption stream.
However, in order to make the results more intuitive, we pres- ent welfare changes in terms of consumption equivalents. The con- sumption equivalent measure defines the constant fraction of consumption that households should give away in order to obtain the benefits of the macroprudential policy. A positive value means a welfare gain, that is, how much the consumer would be willing to pay to obtain the welfare improvement. Then, when there is a wel- fare gain, households would be willing to pay in consumption units for the measure to be implemented because it is welfare improv- ing. We use as a benchmark the welfare evaluated when the mac- roprudential policy is not active and compare it with the welfare obtained when such policy is implemented. The derivation of the welfare benefits in terms of consumption equivalent units is as follows:
CEs ¼ exp ð1 � bsÞ W MP s � W
� s
�h i � 1; ð26Þ
CEb ¼ exp ð1 � bbÞ W MP b � W
� b
�h i � 1; ð27Þ
where the superscripts in the welfare values denote the benchmark case when macroprudential policies are not introduced and the case in which they are, respectively.17
3.2. Welfare trade-offs
The literature typically finds that the macroprudential reaction to exogenous shocks can make some people better off (typically borrowers), but not every type of household, or not in all cases. This is why, welfare comparisons should not only be made on the basis of an ad hoc aggregate welfare function but disaggregat- ing welfare between agents, to highlight the trade-offs that may appear between them.
In this section, we first compute welfare for each individual and for the aggregate, when we have a static LTV. Then, we numerically evaluate welfare gains when we introduce a macroprudential rule, given the Taylor rule.
Fig. 1 presents welfare gains, in consumption equivalents, for different values of the LTV, when there is no macroprudential rule in place. Here, we observe that up to a threshold LTV value, there is
7 We follow Ascari and Ropele (2009).
1
0 0.5 1 1.5 2 2.5 3 3.5 -0.5
0
0.5
1
1.5
2
2.5
phib
W el
fa re
g ai
n (C
E )
Total Savers Borrowers
Fig. 2. Welfare gains from introducing the macroprudential rule, given monetary policy (different values of the reaction parameter for borrowing).
M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336 331
room for Pareto optimal policies. However, starting from a value of 0.55, there is a trade-off between borrowers and savers in terms of welfare when we keep increasing the LTV. Large values of the LTV harm borrowers while savers benefit from the increase. Social wel- fare decreases. This result is in line with that of Campbell and Hercowitz (2009), who performes a welfare analysis in a DSGE model with borrowers and savers and determined that although high LTV ratios have a direct positive effect on welfare through constraint relaxation, other indirect effects may dominate. Notice that k, the LTV ratio, is a parameter that strongly affects the collat- eral constraint. A small change in this parameter can cause very large changes in borrowing that can be excessive. Higher LTVs lead to higher consumption levels, because borrowing constraints are always binding: the more borrowers are offered, the more they take. But this in turn, as shown in Campbell and Hercowitz (2009), changes relative prices. In particular, higher consumption levels imply higher interest rates. This could lead to a situation of overindebtedness in the sense that high repayments could offset the positive effects on constraint relaxation. Then, higher interest rates imply higher returns on saving for savers. Smith (2009) shows that these results do not rely on the specific assumptions of Campbell and Hercowitz (2009); even in the simplest model with borrowers, savers, and collateral constraints, this effect takes place.18
Fig. 2 shows the welfare gains from introducing a macropruden- tial tool in the economy, given the Taylor rule. We use a steady- state value of the LTV of 0.9, as in Iacoviello (2005) and Iacoviello (2013). Therefore, we are in a region in which trade-offs should ap- pear. Leaving fixed monetary policy, we present welfare for a con- tinuum of values of the reaction parameters in the LTV rule, from a less to a more aggressive rule. The figure is very informative be- cause it shows welfare gains for each agent in the economy and for the aggregate. The conclusions we can obtain from the figure are the following: using both policy measures at the same time is unambiguously welfare enhancing, as we can observe from the solid line. We can see that welfare increases by more, the larger the response of the LTV to credit growth is, but up to a point at which welfare stops increasing. The figure also shows the trade- off between borrowers’ and savers’ welfare, illustrated by the dif-
18 Huggett (1997) also found a similar result, but in this case is the reduction in the precautionary motive for saving, driven by the looser borrowing constraints, wha leads to the increase in the interest rate.
19 Andres et al. (2013) find that optimal monetary policy may involve a trade-of between the stabilization of inflation, output gap, consumption gap and the distribution of the collateral asset between constrained and unconstrained
t
ference between the two dashed lines. Borrowers’ welfare in- creases with the introduction of the macroprudential rule because tightening the collateral constraint avoids situations of overindebt- edness in which debt repayments are a burden for them. Further- more, borrowers can benefit from more financial stability in the economy, as we will show later on. Notice that borrowers have a collateral constraint which is always binding and this does not al- low them to make consumption smoothing. They do not have an Euler equation to smooth consumption as savers do. A more stable financial system smooths their consumption path thus mitigating the negative effects of the collateral constraint. This welfare gain is at the expense of savers, who lose from having this measure in the economy, given that they are not financially constrained. How- ever, the borrower’s welfare gain compensates the loss of the sav- ers and globally, the measure is welfare increasing.
The next section performs an optimal policy analysis in order to assess which are the combination of values of the reaction param- eters which would maximize welfare and make policy recommen- dations on this issue.
4. Optimal policy analysis
4.1. Optimal parameters
In this section, we aim to find the optimal combination of policy parameters that maximizes welfare. For this purpose, we consider three different cases. A benchmark case in which there is only a monetary authority that acts in the traditional way, using the interest rate as an instrument. Then, we include a macroprudential authority that introduces an extra instrument, the LTV ratio. We study the interaction between the two authorities from two per- spectives, when they act both in a coordinated and in a non-coor- dinated way.
The optimal policy analysis, in models with financial frictions, deserves some discussion. In the standard new Keynesian model, the central bank aims at minimizing the variability of output and inflation to reduce the distortion introduced by nominal rigidities and monopolistic competition. However, in models with collateral constraints, welfare analysis and the design of optimal policies in- volves a number of issues not considered in standard sticky-price models. In models with constrained individuals, there are two types of distortions: price rigidities and credit frictions. This cre- ates conflicts and trade-offs between borrowers and savers. Savers may prefer policies that reduce the price stickiness distortion. However, borrowers may prefer a scenario in which the pervasive effect of the collateral constraint is softened. Borrowers operate in a second-best situation. They consume according to the borrowing constraint as opposed to savers that follow an Euler equation for consumption. Borrowers cannot smooth consumption by them- selves, but a more stable financial system would provide them a setting in which their consumption pattern is smoother. Therefore, in order to assess the optimality of policies, factors that help bor- rowers smooth their consumption should be included. Studies show that, in these kind of models, financial variables should be in- cluded in the loss function that the policy maker aims at minimizing.19
In the standard sticky-price model, the Taylor rule of the central bank is consistent with a loss function that includes the variability of inflation and output. In order to rationalize the Taylor rule of the macroprudential regulator, we follow Angelini et al. (2012) in which they assume that the loss function in the economy also con-
consumers.
f
Table 1 Optimal macroprudential and monetary policy mix.
Benchmark Coordinated Non-coordinated
/k�b – 0.8 0.7
1 þ /R�p 16.1 1.3 1.7 /R�y 8.2 0.5 1
Social Welfare Gain – 0.024 0.041 Borrowers Welfare Gain – 0.22 0.31 Savers Welfare Gain – �0.16 �0.21 r2b 1.4308 1.1861 1.1767 r2p 0.2183 0.3481 0.3025 r2y 1.9113 1.7877 1.8087
2 Notice that here, we are considering that the central bank acts in a traditional
332 M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336
tains financial variables, namely borrowing variability, as a proxy for financial stability. Then, there would be a loss function for the economy that would include not only the variability of output and inflation but also the variability of borrowing: L ¼ r2p þ kyr2y þ r2b where r
2 p; r
2 y and r
2 b are the variances of infla-
tion, output and borrowing. ky P 0, represents the relative weight of the central bank to the stabilization of output.20
If the central bank and the macroprudential regulator coordi- nate, they would aim at jointly minimizing the loss function each one with its own instrument. The problem becomes analogous to the Mundell’s assignment rule in which each arm of policy concen- trates on a single task, addressing the issue it cares most about, and making coordination of policy trivial.21 Following this line of argu- ment, we consider a case in which we jointly optimize the parame- ters of both rules.
However, Svensson (2012) argues that conducting monetary policy and financial stability policy in an integrated way may be inappropriate, since monetary policy and financial-stability policy are distinct and separate policies with different objectives and dif- ferent instruments. Tinbergen (1952) put forth what we now call the ‘Tinbergen principle,’ that policymakers need at least one inde- pendent policy instrument for each policy objective. Since the pol- icy interest rate is used by monetary policymakers to achieve the objective of price stability, at least one other instrument is required to achieve the additional objective of financial stability of macro- prudential policy. Svensson (2012) suggests that monetary policy should be in charge of price stability while macroprudential policy needs to address financial stability. He argues that monetary policy should be conducted taking the macroprudential policy into ac- count, and vice versa, as in a Nash equilibrium rather than a coor- dinated equilibrium. Therefore, we study a second case in which the central bank and the macroprudential regulator play a non- coordinated game. The central bank would find the optimal param- eters in its policy rule, taking the macroprudential regulator behav- ior as given. Similarly, the macroprudential authority would find the best response given monetary policy. The intersection of these two best responses would give us the Nash equilibrium.
In order to contribute to the discussion and evaluate the welfare gains of introducing macroprudential polices, we first compute the optimal parameters of the Taylor rule for monetary policy, assum- ing that there is no macroprudential regulator. Then, we compute the optimal monetary and macroprudential policies for the coordi- nated and the non-coordinated game.
Table 1 shows the optimal parameter values and the welfare gains in consumption equivalents, taking as a benchmark the situ- ation without macroprudential policy. We also present the implied volatilities.
20 This loss function would be consistent with studies that make a second-order approximation of the utility of individuals and find that it differs from the standard case by including financial variables.
21 See Mundell (1962).
As expected, when a macroprudential regulator does not exist, the central bank needs to act in a very aggressive way, given that it only counts with a single instrument to minimize the loss func- tion.22 We take this case as a benchmark, both for welfare and for macroeconomic and financial volatilities (presented in the first column).
The second column presents the case in which there is a macro- prudential regulator that acts in a coordinated way with the cen- tral bank. We see that adding this extra instrument produces a welfare gain in the economy. In this case, monetary policy does not need to be as aggressive as in the benchmark case because it counts with the help of the macroprudential policy. However, as al- ready pointed out, there is a trade-off between borrowers and sav- ers and, while borrowers are better-off, savers are not. Furthermore, if we compare the volatilities that this combination of policies generates, with respect to the benchmark case, we ob- serve that the standard deviation of borrowing decreases, which is what makes borrower’s welfare increase. In terms of the macro- economic volatilities, we see that the volatility of output decreases, but this comes at the expense of a higher inflation volatility.23 This higher inflation volatility contributes to a decrease in savers’ welfare.
Nevertheless, if both authorities act in a non-coordinated way, social welfare gains are even higher. As Svensson (2012) argues, letting each regulator focus on its own objective, leads to more effective results in reducing volatilities. In this case, monetary pol- icy acts in a more aggressive way, favoring the reduction of the vol- atility of inflation. The macroprudential authority reaction parameter does not need to be as high as in the previous case to obtain a lower standard deviation of borrowing. As usual, we also observe the same trade-off between borrowers and savers.
4.2. Pareto-superior outcomes
Results from optimal policy analysis show that trade-offs be- tween the two agents appear. However, if the welfare gain that borrowers obtain is large enough, there could be room for Pare- to-superior outcomes.
In order to do that, we apply the concept of Kaldor–Hicks effi- ciency, also known as Kaldor–Hicks criterion.24 Under this criterion, an outcome is considered more efficient if a Pareto-superior out- come can be reached by arranging sufficient compensation from those that are made better off to those that are made worse off so that all would end up no worse off than before. The Kaldor–Hicks cri- terion does not require the compensation actually being paid, merely that the possibility for compensation exists, and thus need not leave each at least as well off.
In our case, our measure for welfare presented in consumption equivalents is given by Eqs. (26) and (27). Since, there is a trade-off between savers and borrowers, introducing the macroprudential policy, both in coordination and non-coordination with monetary policy, produces CEb > 0 and CEs < 0.
Thus, a Kaldor–Hicks improvement to a obtain Pareto-superior outcome would be one in which:
CEb � eb P 0
and
CEs þ eb ¼ 0:
ay, we are excluding the possibility that financial variables enter in the Taylor rule r the central bank. For further discussion on interactions between different rules, e Kannan et al. (2012) or Rubio and Carrasco-Galllego (2013). 3 This result is consistent with other studies on macroprudential policies. See for stance, Mendicino et al. (2013). 4 See Scitovsky (1941).
2
w fo se
2
in 2
Table 2 Optimal macroprudential and monetary policy mix (Kaldor–Hicks improvement).
Benchmark Coordinated Non-coordinated
/k�b – 0.8 0.7
1 þ /R�p 16.1 1.3 1.7 /R�y 8.2 0.5 1
Social Welfare Gain – 0.024 0.041 Borrowers Welfare Gain – 0.06 0.10 Savers Welfare Gain – 0 0
Table 3 Parameter values.
bs :99 Discount factor for savers bb :98 Discount factor for borrowers j :1 Weight of housing in utility function g 2 Parameter associated with labor elasticity k :9 Loan-to-value ratio a :64 Labor share for savers X 1:2 Steady-state markup h :75 Probability of not changing prices qA :9 Technology persistence qj :95 Housing demand shock persistence q :8 Interest-rate-smoothing parameter in Taylor rule
M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336 333
Then,
eb P 1 � exp ð1 � bsÞ W MP s � W
� s
�h i : ð28Þ
That is, a system of transfers in which the borrowers would compensate the savers with at least the amount they are losing, so that they are at least indifferent between having the macropru- dential policy or not. Then, the new outcome would be desirable for society and there would be no agent that would lose with the introduction of the new policy. Then, if Eq. (28) holds with equal- ity, the borrower compensates the saver with the exact welfare that she is losing. Then, in our case, after the compensations are made, the final result is presented in Table 2.
4.3. Impulse responses
In order to understand the dynamics of the model and how the LTV rule interacts with monetary policy, in this section, we simu- late the impulse responses of the model, using the optimized parameters we found in the previous section. We compare the benchmark (no macroprudential policy) with the case in which monetary and macroprudential policies coexist, both in a coordi- nated and in a non-coordinated game. We consider a technology shock and a housing demand shock.
The discount factor for savers, bs, is set to 0.99 so that the an- nual interest rate is 4% in steady state. The discount factor for the borrowers is set to 0.98.25 The steady-state weight of housing in the utility function, j, is set to 0.1 in order for the ratio of housing wealth to GDP to be approximately 1.40 in the steady state, consis- tent with the US data. We set g ¼ 2, implying a value of the labor supply elasticity of 1.26 For the parameters controlling leverage, we set kSS to 0.90, in line with the US data.
27 The labor income share for savers is set to 0.64, following the estimate in Iacoviello (2005). For the Taylor rule, we consider the optimized parameters found in the previous section. For q we use 0.8, which also reflects a real- istic degree of interest rate smoothing.28
We assume that technology, At , follows an autoregressive pro- cess with 0.9 persistence and a normally distributed shock. We also assume that the weight of housing on the utility function is equal to its value in the steady state plus a shock which follows an auto- regressive process with 0.95 persistence.29 For the reactions param- eter in the LTV rule, we use the optimized parameters both for the coordination and non-coordination with monetary policy. Table 3 presents a summary of the parameter values used:
4.3.1. Technology shock Fig. 3 presents impulse responses to a 1% shock to technology.
Given the technology shock, output increases and inflation decreases.
In the benchmark case, when there is only monetary policy, the interest rate increases, while the LTV remains at its steady state. Since output is increasing, monetary policy reacts in a contractive way. Given the expansion in the economy, borrowing and housing demand increase, leading to an increase in house prices.
However, when the macroprudential rule interacts with mone- tary policy, the reaction of the interest rate is not as strong, given that the optimal parameters of the Taylor rule are lower. The LTV
25 Lawrance (1991) estimated discount factors for poor consumers at between 0.95 and 0.98 at quarterly frequency. We take the most conservative value.
26 Microeconomic estimates usually suggest values in the range of 0 and 0.5 (fo males). Domeij and Flodén (2006) show that in the presence of borrowing constraints these estimates could have a downward bias of 50%.
27 See Iacoviello (2013). 28 As in McCallum (2001). 29 The persistence of the shocks is consistent with the estimates in Iacoviello and
Neri (2010).
r
ratio decreases to cut credit because borrowing is growing follow- ing the boom. Therefore, when the macroprudential rule is in place, borrowing does not increase as much as in the benchmark, and this mitigates the effects of the boom.
Concerning the difference between the coordinated and the non-coordinated case, the pattern of the impulse responses is very similar. Nevertheless, the non-coordinated case is always slightly closer to the benchmark. This is due to the fact that the reaction parameters in the Taylor rule are higher for the coordinated case and thus more similar to the benchmark.
Notice that, interestingly, when monetary and macroprudential policies coexist, the interest rate decreases, focusing on stabilizing inflation, while the LTV is cut, to reach the financial stability objec- tive. The decrease in the interest rate contributes to increase bor- rowing while the decrease in the LTV cuts it.
4.3.2. Housing demand shock In Fig. 4, we see the effects of a 25% housing demand shock. Gi-
ven the increase in demand, house prices increase as well. This di- rectly affects the collateral constraint and borrowers are able to borrow more out of their housing collateral, which is worth more now. The wealth effect permits them consume both more houses and consumption goods. The increase in house prices is, therefore, transmitted to the real economy and output increases.
The raise in output generates inflation and the Taylor rule re- sponds with a higher interest rate. This is particularly true in the benchmark case in which monetary policy is more aggressive. On impact, this higher interest rate also dampens the increase in the price of the house, especially for the benchmark for the same rea- sons. Therefore, the initial shock is mitigated in the case in which monetary is the only policy in action.
When the macroprudential and the monetary policy interact, the LTV decreases to moderate the credit boom. This is the reason why, in this case, borrowing does not increase as much as in the benchmark. However, as we have seen, the increase in the interest rate is not as strong as in the benchmark and therefore the effects on real output of this demand shock are more noticeable. In the case of this shock, the combination of the macroprudential and the monetary policies manage to control credit without moderat- ing the real effects of the boom.
0 5 10 0
0.5
1 Output
% de
v. S
S 0 5 10
0
0.5
1 Borrowing
0 5 10 −0.5
0
0.5
Inflation %
de v.
S S
0 5 10 0
0.5
1
House Prices
0 5 10 −0.2
0
0.2
Interest Rate
quarters
% de
v. S
S
0 5 10 −0.2
0
0.2
LTV
quarters
Benchmark Coordinated Macropru Non−coord Macropru
Fig. 3. Impulse responses to a technology shock. Optimized parameters.
0 5 10 0
0.05
0.1 Output
% de
v. S
S
0 5 10 0
2
4 Borrowing
0 5 10 −0.1
0
0.1 Inflation
% de
v. S
S
0 5 10 0.2
0.3
0.4 House Prices
0 5 10 0
0.05
0.1 Interest Rate
quarters
% de
v. S
S
0 5 10 −0.5
0
0.5 LTV
quarters
Benchmark Coordinated Macropru Non−coord Macropru
Fig. 4. Impulse responses to a housing demand shock. Optimized parameters.
334 M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336
As in the previous case, and for the same reasons, the non-coor- dinated situation is closer to the benchmark.
0 See for instance Iacoviello (2005) that evaluates a Taylor rule responding to house rices with a policy frontier.
4.4. Financial and macroeconomic stability
Results from the optimal policy analysis have shown that the combination of macroprudential and monetary policies deliver a more stable financial and macroeconomic scenario. In order to show these results graphically, we plot an efficiency frontier that includes the three objectives that the policy makers aim at mini- mizing: variability of output, variability of inflation and variability of borrowing.
Policy analysis is usually done through policy frontiers, also known as Taylor curves or efficiency frontiers.30 This curve shows, given different parameters of the Taylor rule, the combination that delivers the lower output and inflation variability. Therefore, a Tay- lor curve which is closer to the origin would be more efficient. In or- der to include the objective of the macroprudential regulator, we present an extended Taylor curve in which we include the variability of borrowing, as a measure to capture financial stability.
We are aware that there is not a widely accepted definition of financial stability or systemic risk. Those are difficult concepts to
3
p
3 4
5 6
7 8
1.4
1.6
1.8
2 50
100
150
200
250
300
output varianceinflation variance
bo rr
ow in
g va
ria nc
e
Benchmark Coordinated Macropru Non−coord Macropru
Fig. 5. Three dimensional efficiency frontier.
M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336 335
define and to measure. Many definitions include the interactions between the financial and the real sector.31 In our model, we char- acterize the financial sector implicitly: borrowers take credits from savers and sign mortgages to buy houses, the asset of our model. Therefore, the financial system can be proxied by the amount of bor- rowing that takes place. Within this framework, we propose a mea- sure for financial stability: a low variability of borrowing. In this sense, a lower variance of borrowing would imply a more stable financial system: if the variance of borrowing is lower, credit is smoother. A more stable financial system contributes to a lower sys- temic risk. Our model fits this idea. Borrowers do not have an Euler equation that allows them to smooth their consumption, as savers do. If the variability of the borrowing is lower then borrowers can sign mortgages in a smoother way and also can achieve a more sta- ble consumption. The financial sector will be more stable and also the real sector. The economy can benefit from a more stable financial system and a lower systemic risk with a higher welfare, as we proved in previous sections. However, if the situation is the opposite and there is a high variability of borrowing, the financial system will be more unstable: with credit being more variable, consumption would also be more variable, the systemic risk will increase and, therefore, welfare will be lower.
Fig. 5 presents our augmented policy frontier which is three- dimensional, since it takes into account three policy objectives: output, inflation and financial stabilization. The first two corre- spond to the standard objectives of the central bank, while the third one would be the objective of the macroprudential regulator. As in previous cases, we are comparing the macroprudential (coor- dinated and non-coordinated) with the no macroprudential sce- nario (benchmark). Here, curves are preferable, the lower (less borrowing variance) and closer to the inflation and output variance origin (less inflation and output variability) they are. We see that when we take the three dimensions together, macroprudential and monetary policies interacting with each other manage to deli- ver a more stable scenario, which includes not only macroeco- nomic stability but also financial stability. These results represent a way to convey the findings in previous sections, that is, the introduction of the macroprudential policy is welfare enhancing because it is delivering a more stable system.
5. Concluding remarks
In this paper, we analyze the impact of macroprudential and monetary policies on business cycles, welfare, and financial stabil-
31 See Galvão and Owyang (2013) for a discussion on the topic.
ity. In particular, we consider a macroprudential rule for the LTV ratio that responds to credit growth.
We compute the optimal parameters of the macroprudential and monetary rule both when monetary and macroprudential pol- icies act in a coordinated and in a non-coordinated way. We find that in both cases, this interaction is welfare improving for the society, especially in the case of the non-coordinated game. How- ever, there is a trade-off between the agents of the model and sav- ers lose from this new scenario. We find that by transfers �a la Kaldor–Hicks, so that borrowers can compensate the saver’s wel- fare loss, a Pareto-superior outcome can be obtained.
From a positive perspective, we show the dynamics of the mod- el under the optimal parameters that maximize welfare. We find that, given a positive technology or housing demand shock, the macroprudential authority would decrease the LTV to moderate the credit boom. In this way, it can achieve its ultimate goal: finan- cial stability.
We also show graphically, with a three dimensional policy fron- tier, that the interaction between monetary and macroprudential policies unambiguously enhances the stability of the economic system.
Acknowledgments
We would like to thank the discussants and participants of IRE- BS Conference 2012, 2012 Dynare Conference, ReCapNet Confer- ence 2013, CEUS Workshop 2013, IFABS Conference 2013, and AREUEA session at the ASSA Meetings 2014; as well as the seminar participants at the Bank of England, the Federal Reserve Board, the Federal Reserve Bank of St. Louis, the Central Bank of Luxembourg, the BBVA, and the University of Nottingham. Special thanks to Mat- teo Iacoviello, John Duca, William Dupor, Pau Rabanal, Carlos Tho- mas, Antonio Mele, Don Schlagenhauf, Daniel Fetter, Christopher Otrok, Rafael Repullo, Jagjit S. Chadha, and two anonymous refer- ees. All errors are our own. J. A. Carrasco-Gallego would also like to acknowledge the financial support of Universidad Rey Juan Car- los Fellowship for International Research Stays to visit the Univer- sity of Nottingham.
Appendix A. Main equations
1 Cs;t ¼ bs Et
Rt ptþ1 Cs;tþ1
� � ; ð29Þ
wst ¼ðNs;tÞ g�1Cs;t; ð30Þ
j Hs;t ¼
1 Cs;t
qt � b sEt
1 Cs;tþ1
qtþ1; ð31Þ
1 Cb;t ¼ bb Et
Rt ptþ1 Cb;tþ1
� � þ kt Rt; ð32Þ
wb;t ¼ðNb;tÞ g�1 Cb;t; ð33Þ
j Hb;t ¼
1 Cb;t
qt � b bEt
1 Cb;tþ1
qtþ1
� � � kbt kt Etðqtþ1ptþ1Þ; ð34Þ
Et Rt
ptþ1 bt ¼ kt Et qtþ1 Hb;t; ð35Þ
Cb;t þ qt Hb;t þ Rt�1 bt�1
pt ¼ qt Hb;t�1 þ wb;t Lb;t þ bt; ð36Þ
ws;t ¼ 1 Xt
a Y t
Ns;t ; ð37Þ
wb;t ¼ 1 Xt ð1 � aÞ
Y t Nb;t
; ð38Þ
336 M. Rubio, J.A. Carrasco-Gallego / Journal of Banking & Finance 49 (2014) 326–336
p̂t ¼ bEtp̂tþ1 � wx̂t þ upt; ð39Þ
W s;t � Et X1 m¼0
bms log Cs;tþm þ j log Hs;tþm � ðNs;tþmÞ
g
g
� � ; ð40Þ
W b;t � Et X1 m¼0
bmb log Cb;tþm þ j log Hb;tþm � ðNb;tþmÞ
g
g
� � ; ð41Þ
W t ¼ð1 � bsÞW s;t þð1 � bbÞW b;t: ð42Þ
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- Macroprudential and monetary policies: Implications for financial stability and welfare
- 1 Introduction
- 1.1 Related literature
- 2 Model setup
- 2.1 Savers
- 2.2 Borrowers
- 2.3 Firms
- 2.3.1 Final goods producers
- 2.3.2 Intermediate goods producers
- 2.4 Monetary policy
- 2.5 A macroprudential rule for the LTV
- 2.6 Equilibrium
- 3 Welfare
- 3.1 Welfare measure
- 3.2 Welfare trade-offs
- 4 Optimal policy analysis
- 4.1 Optimal parameters
- 4.2 Pareto-superior outcomes
- 4.3 Impulse responses
- 4.3.1 Technology shock
- 4.3.2 Housing demand shock
- 4.4 Financial and macroeconomic stability
- 5 Concluding remarks
- Acknowledgments
- Appendix A Main equations
- References
Monetary Policy and Asset Price Interactions in India Should Financial Stability Concerns.pdf
Monetary Policy and Asset Price Interactions in India: Should Financial Stability Concerns from Asset Prices be Addressed Through Monetary Policy? Author(s): Bhupal Singh and Sitikantha Pattanaik Source: Journal of Economic Integration, Vol. 27, No. 1 (March 2012), pp. 167-194 Published by: Center for Economic Integration, Sejong University Stable URL: http://www.jstor.org/stable/41473736 . Accessed: 13/02/2015 16:36
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Journal of Economic Integration 27(1), March 2012; 167-194
Monetary Policy and Asset Price Interactions in India:
Should Financial Stability Concerns from Asset
Prices be Addressed Through Monetary Policy?
Bhupal Singh Reserve Bank of India
Sitikantha Pattanaik Reserve Bank of India
Abstract
The dynamic interactions between monetary policy and asset prices have
conventionally been examined in terms of the asset price channel of transmission
of monetary policy, given the pre-crisis analytical consensus against the use of monetary policy to respond directly to asset price inflation. In the post sub-prime crisis period, however, there has been an overwhelming intellectual support for revisiting the issue of whether monetary policy should become more sensitive to asset price trends and respond proactively to prevent any build up of bubbles. In the Indian context, this paper provides empirical evidence to explain the relevance
of a policy of no direct use of the interest rate instrument for stabilising asset price
cycles. While the asset price channel of monetary policy is clearly visible in
empirical estimates, there is no evidence of monetary policy responding to asset
price developments directly. Asset price changes also do not seem to influence the
inflation path, as per the impulse response analysis in a structural VAR model. This suggests why monetary policy may continue to refrain from responding directly to asset price cycles. Credit market shocks, however, explain significant
♦Corresponding address: Bhupal Singh; Reserve Bank of India (RBI), Department of Economic and Policy Research(DEPR), Central Office, Saheed Bhagat Singh Road, Fort Mumbai, India. / Sitikantha Pattanaik; Reserve Bank of India (RBI), Department of Economic and Policy Research(DEPR), Central Office, Saheed Bhagat Singh Road, Fort Mumbai, India. E-mail : [email protected].
©2012-Center for Economic Integration, Sejong Institution, Sejong University, All Rights Reserved.
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1 68 Bhupal Singh and Sitikantha Pattanaik
proportion of asset price variations over medium to long run, which though could
be part of a broader comovement of variables over the business cycle, as visible
in terms of simultaneous movement in real activity, credit flows and asset prices.
Higher interest rates seem to lead to contraction in output, credit demand as well
as asset prices; hence, only the impact on asset prices should not be viewed as a
good enough reason to use monetary policy for stabilising asset price cycles. The
financial stability concerns from asset price bubbles could be better addressed
through micro and macro-prudential measures, and the effectiveness of such
measures could be enhanced when implemented in a sound macroeconomic policy environment.
• JEL Classification: C33, E52
• Keywords: Monetary Policy, Asset Prices, VAR Model
I. Introduction
The price stability objective pursued by the central banks is generally defined in
a manner that excludes asset prices. Asset price is often viewed by the central banks
as another macroeconomic variable which could potentially influence the inflation
path either by impacting inflation expectations, or through the wealth effect on
aggregate demand, or by altering the cost of funds. The relationship between
monetary policy and asset prices has been conventionally analysed through the
asset price channel of monetary policy transmission, under which asset prices
respond to monetary policy changes and thereby may impact the ultimate policy
goals relating to inflation and output. The pre-crisis mainstream view on why a
central bank should not directly aimed at containing asset price inflation was
premised on certain sound arguments: (a) bubbles are hard to differentiate from
genuine bull runs, and central banks have no comparative advantage over the
markets to come to any credible conclusion on the fundamental value of assets, (b)
monetary policy instruments could be ineffective in preventing asset bubbles,
particularly speculative bubbles, as the magnitude of the increase in interest rates
would have to be large enough to be able to prick a bubble, which in turn would
entail large loss of output, and (c) central banks have no mandate on asset prices. As a result, the pre-crisis emphasis in monetary policy strategies was to manage the
impact of asset price developments on inflation and growth, whether in a forward
looking manner by anticipating the impact on the inflation outlook, or by reacting to
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Monetary Policy and Asset Price Interactions in India 169
the impact on output and inflation when it becomes visible after the bubble bursts.
The emerging perception after the global crisis is that central banks can
contribute to preventing the build up of asset bubbles by: (a) avoiding credit
bubbles, persistent excess liquidity conditions and build up of leveraged positions in asset markets, and (b) using prudential regulation in terms of counter cyclical
provisioning, counter cyclical risk weights for capital requirement, limiting the
maximum exposure of banks to sensitive assets and prescribing margin
requirements (or loan to value ratio). While the former falls in the domain of
monetary policy, the latter belongs to the purview of financial regulation. The focus
of this paper is on what monetary policy per se could do about asset price inflation, rather than whether a central bank could use instruments other than the interest rate
to stabilise asset price cycle. Against this background, Section II of the paper
presents the academic debate on the role of monetary policy in relation to asset
prices, with a review of literature that reflects the pre-crisis consensus view as well
as the lack of consensus after the global crisis. The issue of whether monetary
policy should be assigned any role relating to asset prices in India has been
evaluated through various empirical tests for India in Section III, not withstanding data limitations in conducting empirical research involving housing assets in India.
Concluding observations are outlined in Section IV.
II. Monetary Policy and Asset Prices - the Debate
Monetary policy actions could get transmitted through changes in financial
prices (e.g. interest rates, exchange rates and asset prices) and financial quantities
(e.g. money supply and credit aggregates), which in turn may influence the
ultimate goal variables, namely inflation and output. The reverse causation may also be significant since monetary policy actions are often based on feedbacks
received from the lead indicators of macro-financial conditions, given that
monetary policy has to be forward looking, recognising the long and variable lags. In this expected bi-directional causality in the interactions between monetary
policy and asset prices, clarity on the role of monetary policy with respect to asset
prices becomes important. In the first type of causation running from monetary
policy action, asset prices may change, but the objective of policy change could be
to attain the ultimate goals relating to inflation or output. Any asset price changes that may take place in this process would be just coincidental, not intentional. Once
monetary policy actions intentionally start targeting asset prices it could necessarily
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1 70 Bhupal Singh and Sitikantha Pattanaik
involve sacrifice of growth and inflation objectives. That is because the magnitude of the increase in interest rate would have to be large enough to effectively pop an asset price bubbles. If that happens, output could contract and deflation fears could
creep in. Thus, all objectives of monetary policy, i.e., not only those relating to
output and inflation, but also financial stability could get sacrificed. The second type of causation, which could be seen in terms of an interest rate
policy rule function, largely remains hypothetical, since following the pre-crisis consensus, no direct feedback from asset prices seems to have triggered any change in policy interest rates of any major central bank. Asset prices may only indirectly condition an interest rate action, through the impact on output and
inflation, for which the wealth and income effects of asset price changes would have to be significant.
After the global crisis, those who proposed a "lean against the wind" role for
monetary policy seem to suggest a place for asset prices directly in the interest rate
policy rule function. Since credit bubbles and excessive leverage could be the
driving forces behind asset price bubbles, either asset prices directly or credit and
leverage as lead indicators of asset prices would then have to find explicit place in the monetary policy reaction function. This is premised on two broad arguments: (i) Given the endogenous money supply process, in which money and credit
growth may be largely demand driven, central banks could change the credit conditions or discourage excessive leverage only by changing the interest rates. Use of macro-prudential measures or sector specific credit/prudential policies could attain the goal, but these are not monetary policy measures. Hence, any role for
monetaiy policy should be seen only through the interest rate rule, where interest rate would respond directly to asset price trends; (ii) Taking a view on asset price bubble or credit bubble should not be difficult for a central bank, since they in any case take views on "potential output" and "threshold inflation" for changing their
policy interest rates, and such estimates are not free of errors. Only the extent of error in judgement could be higher for asset prices or credit bubbles, compared to errors in estimating potential output and threshold inflation. Moreover, if central banks can use macro-prudential regulation, they have to take a view on the extent of misalignment in asset prices, to be able to alter the risk weights for capital adequacy purpose or assign specific provisioning requirements in proportion to the extent of risk expected from exposures to asset price volatility. Thus, the pre-crisis presumption that asset bubbles are hard to identify might have helped central banks to avoid any use of interest rate instrument in pursuit of asset price objective, but
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Monetary Policy and Asset Price Interactions in India 171
given the overwhelming emerging support for use of macro-prudential regulation to promote systemic financial stability, specific views would have to be taken by the central banks on asset prices. The dominant remaining argument against the use
of interest rate instrument, then, would have to be based on the bluntness of the
instrument, which can limit the asset prices from growing into a bubble only at the
expense of sacrificing output and inflation objectives. Thus, for use of macro-prudential regulation, a central bank may have to
necessarily take a view on asset prices, but this assessment need not feed into
decisions on changes in policy interest rates. A Central Bank empowered with the
instrument of macro-prudential regulation may start "leaning against the wind" but
in pursuing this objective, the interest rate instrument may still have no role to play. Thus, the pre-crisis consensus may still be relevant after the global crisis, even
though convincing counter arguments have been expressed, some of which are
mentioned in the review of literature.
A. Review of the literature
Theoretical and empirical research appears more divided after the global crisis
on the issue of role of monetary policy relating to asset price developments. A rich
body of literature prior to the global crisis seemed to support the argument that a
monetary policy approach which responds primarily to the inflation and aggregate demand outlook rather than directly trying to prick the bubble is likely to yield better macroeconomic outcomes (Bernanke, Gertler and Gilchrist, 1999; Bernanke
and Gertler, 2001; Gruen, Plumb and Stone, 2005). The pre-crisis consensus
reflected the famous Greenspan orthodoxy on asset price build-up that argues that
it is hard to identify bubbles ex ante and central banks may not have better
information than markets to influence asset prices.1 Further, even if a bubble can be
identified ex ante, using the interest rate is ineffective in bursting a bubble.2
Similarly, monetary policy response to tackle an asset boom can interfere with the
role of asset prices in allocating resources, particularly if there is uncertainty with
regard to the presence and nature of a bubble. The asset bubbles are broadly
explained as asset prices rising above the level warranted by economic
1 Bernanke and Gertler (2001) argued that central banks should disregard asset prices in their policy formulation. They found little, if any, additional gains from allowing an independent response of central bank policy to the level of asset prices. 2Mishkin (2008) opined that since it is difficult to identify asset price bubbles with certainty, any monetary policy response to misidentified bubbles may hamper the growth process.
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1 72 Bhupal Singh and Sitikantha Pattanaik
fundamentals, as measured by the discounted stream of expected future cash flows that will accrue to the owner of the asset.3 The difficulties in identifying asset price bubbles arise mainly from two factors: first, private agents' subjective expectations are the key determinant of asset prices, particularly in the short run, posing difficulties in disentangling the purely psychological component from the objective valuation of the asset; second, asset bubbles often arise from overreactions to news about fundamentals.4
Given the difficulties in identifying asset price bubbles, the best course for
monetary policy could be to cushion the adverse impact once the bubble bursts
(Bean, 2003; Bernanke and Gertler, 1999, 2001; Blinder and Reis, 2005; Bordo et
al., 2002, 2003; Bordo and Wheelock, 2004, Filardo, 2004; Greenspan, 2002; Roubini, 2006). For equity prices to be a useful monetary policy indicator, a credible relationship between changes in monetary policy and changes in equity prices as well as between changes in equity prices and changes in inflation should be established (Saxton, 2003). Empirical investigations, however, do not seem to offer a reliable relationship between changes in monetary policy and equity prices. Mishkin and White (2002) argued that most fluctuations in stock prices occur for reasons not associated with monetary policy, either reflecting real fundamentals or animal spirits. The loose link between monetary policy and stock prices, therefore,
implies the limited ability of central banks to control stock prices. Similarly, there does not seem to be a reliable positive empirical relationship between changes in
equity prices and changes in general price levels (Filardo, 2000; Goodhart and
Hofmann, 2000; Stock and Watson, 2001; Tatom, 2002). Moreover, the
consumption and investment sensitivity to the wealth effect of equity and housing prices, despite their growing share in the household wealth and the economy, may be relatively weak (Grämlich, 2001; Kuttner and Mosser, 2002; Ludvigson and
Lettau, 2002).
3Key features of asset prices that are associated with bubbles could be best analysed in the framework of forward looking general equilibrium models with the assumptions of rational behaviour and infinite horizons. Thus, the rational bubbles reflect expectations of rising prices that can lead to self-fulfilling equilibrium outcomes, with the following expectational restriction (Filardo, 2004): E,/2,+l = X£2b ADA The rational asset bubbles tend to develop without link to fundamentals since the holders of speculative asset experiencing bubbles are also guided by the expectation of persistent rise in the price of that asset. Such bubbles are identified as generating significant persistent overvaluation or undervaluation of asset prices due to excessive reaction to fundamentals (Froot and Obsfeld, 1991). "The difficulties involved are extracting information from a constellation of asset prices, which would require disentangling risk premia from expectations component, identifying relevant state variables that enter the asset pricing and determining the functional form of the pricing relationship (Hordahl and Packer, 2007).
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Monetary Policy and Asset Price Interactions in India 1 73
After the global crisis, influential opinions have supported the need for making central banks more sensitive to asset price developments in the conduct of their
monetary policies, even though justifications for the relevance of the pre-crisis
approach also continue to be significant. There was a "lean against the wind"
perspective even before the global crisis, which argued that central banks should
explicitly respond to perceived asset price bubbles, even if that involves short run
deviations of monetary policy from the path conditioned by the inflation-growth
objectives (Bordo and Jeane, 2002; Borio and Lowe, 2002; Cecchetti et al, 2000;
Crockett, 2001; Detken and Smets, 2004; Filardo, 2000; Roubini, 2006). It was
also observed that monetary policy could identify the bubble component from the
fundamental component in asset prices and the optimal monetary policy could
react more to the bubble than to the fundamental component of asset prices
(Rudebusch, 2005).5 The pre-crisis perception of the best practice in monetary policy framework as
the one characterised by a single target (i.e., price stability) and a single instrument
(i.e., short-term policy interest rate) has generally been questioned on the ground that a less inflation-centric and more asset price sensitive monetary policy could
possibly have been more appropriate as a crisis preventive mechanism. Even
though sustained easy monetary conditions have been highlighted as a causative
factor behind the asset price bubbles, empirical estimates suggest that the stance of
monetary policy has not generally been a good leading indicator of future busts in
asset prices, "...loose monetary policy was not the main, systematic cause of the
boom and consequent bust" (IMF, WEO, 2009). One of the key arguments in the debate on the dynamics between monetary
policy and asset prices has been that monetary policy should respond to asset
prices only to the extent of their impact on growth, employment and inflation, which are the core objectives of monetary policy (Kohn, 2008). This requires an
understanding of how asset prices influence inflation and economic activity. Some
have argued that the impact of asset prices on aggregate demand and inflation
should fall within the domain of monetary policy. But this perspective is not new, and was known to central banks even before the crisis. Another area that has been
argued to fall in the domain of monetary policy is the asset price bubble that may be fuelled by excessive credit growth. The feedback loop between credit growth
5At the same time, it was viewed that mere escalation of asset price may be an insufficient indicator of asset price bubbles.
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1 74 Bhupal Singh and Sitikantha Pattanaik
and asset price growth could potentially pose challenges for the inflation and
growth objectives of central banks. Hence, it is aigued that monetary policy should
respond to asset price bubbles that are propagated by excessive credit expansion in
the economy (Blinder, 2008). Another argument is that asset price bubbles can
have serious adverse macroeconomic consequences and therefore, it is preferable to tiy to eliminate the source of macroeconomic instability directly by adopting a
policy of leaning against the wind. Since central banks are generally held
responsible for financial stability even without any explicit mandate, they should
monitor asset prices and tiy to prevent the emergence of bubbles (that invariably lead to financial crashes).6 Interest rate could be an effective tool in preventing bubbles (Orphanides, 2010; Papademos, 2009).
From a pragmatic policy perspective, however, it is still largely ambiguous as to
how monetary policy could respond to asset prices directly, even if it is presumed that it must in some way. Trichet (2009) noted that "...central banks should not
target, nor react mechanically to asset prices. Judgement is necessary in addressing asset price dynamics within an overall framework geared to price stability." Donald
Kohn (2008) viewed that "...I am not convinced that the events of the past few
years and the current crisis demonstrate that central banks should switch to trying to check speculative activity through tighter monetary policy whenever they
perceive a bubble forming. . .the case for extra action still remains questionable." There is also a lack of political mandate for central banks to control asset prices. With no instrument to target successfully asset prices, by pricking a bubble, a
central bank can also create macroeconomic instability and ruin its credibility
(Issing, 2009). Whether any specific mandate on asset prices for central banks
could undermine central bank independence is an issue which has not been examined very seriously as yet, but the risk to independence cannot be ruled out
given that there will be some interest groups that may benefit from asset price inflation, whether genuine or speculative.
Given the inherent practical limitations of monetary policy in dealing with asset
prices, other policies that could be effective in ensuring financial stability include
regulatory policies and the fiscal policy.7 The regulatory policy instruments to deal
6Excessively accommodative monetary policy may not be immediately reflected in consumer prices given the existence of nominal rigidities in the economy, and hence may be first visible in the asset price increases. Importantly, in case of housing market, given the transmission lags of monetaiy policy, interest rate increases are unlikely to be effective in the short run, therefore, special regulatory measures could be more effective (Savoir and Bangui, 2006).
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Monetary Policy and Asset Price Interactions in India 1 75
with asset bubbles may comprise limits on the credit exposure to real estate and
stock markets, enhancement of relative risk weights/provisioning for bank lending,
monitoring of banks' investment in asset markets through special purpose vehicles,
counter-cyclical loan to value limits, caps on leverage, and tighter eligibility and
collateral requirements on loans for investment in particular assets. Fiscal policy can also work as a countercyclical tool to influence asset price movements through
countercyclical public expenditure plans and also suitable adjustment of taxes/ tax
exemptions that could influence asset prices. Changes in tax incentives to the real
estate sector or investments in financial instruments such as mutual funds and
equity over long-term that alters effective return on such instruments may help in
containing excessive asset price growth. Use of transaction tax on assets where
there is excessive speculation, including Tobin-type taxes when speculative foreign
capital inflows are perceived to lead to destabilising growth in asset prices have
also been advocated.8 As marginal changes in interest rates cannot have much
influence on asset prices, particularly when the expected returns on stock/housing assets significantly exceed the cost of borrowed funds, sector specific prudential
policies could be more appropriate.
III. Monetary Policy and Asset Price Dynamics in India
The empirical assessment for India focuses on the interactions between
monetary policy and housing and stock prices. Equity and housing prices have the
tendency to be procyclical in nature, as high growth phases are generally associated
with an underpricing of risk (Barsky and DeLong, 1993). Four specific issues
empirically examined are: (a) whether asset prices exhibit any causal influence on
the interest rates, which would be relevant to explain whether monetary policy has
responded directly to asset prices in India; (b) whether asset price changes
significantly alter the inflation path - which could be important to examine the
relevance of an indirect role for monetary policy given the extent to which current
asset price trends may alter the inflation outlook; (c) whether interest rate changes lead to expected changes in stock prices alone or also give rise to changes in output and credit demand, which would be important to examine the potential adverse
effects of a hypothetical direct use of monetary policy to deal with asset price
8 The literature, however, highlights that the long run effectiveness of such transactions taxes is limited. Even in the short run, the effectiveness of such measures could be circumvented.
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1 76 Bhupal Singh and Sitikantha Pattanaik
Table 1. Causal relationship between interest rate changes in stock prices. Null Hypothesis F-Statistic Prob. Yield on 9 1 -day TBs do not Granger cause change in stock prices 3.51 0.03 Change in stock prices do not Granger cause yield on 91 -day TBs 1.93 0.15 Yield on 10-year government bonds do not Granger cause change in stock prices 3.56 0.03 Change in stock prices do not Granger cause yield on 1 0-year government bonds 0.49 0.6 1
inflation; and (d) whether the relationship between interest rate changes and asset
prices could be ambiguous because of the presence of other common factors which
may exhibit strong co-movement with both interest rate and asset prices.
A. Monetary policy and asset price cycles
With the short-term interest rate emerging as the predominant instrument of
monetary policy, the interest rate channel of transmission has received significant research focus, even though both asset price and exchange rate channels have become increasingly relevant. A Granger causality analysis of movement in interest rates and changes in stock prices in India for the period 1994:4 to 2010:6 reveals that while interest rate movements cause changes in stock prices, the reverse causation does not hold (Table 1). This seems to suggest that monetary policy does not respond to stock prices, though stock prices respond to monetary policy shocks.
The literature also highlights the possible presence of feedback loops between asset price bubbles and excessive growth in bank credit.9 Unlike stocks, real estate, i.e., both residential and commercial, may have a significant credit component. It is often viewed that if asset bubbles are fuelled by expansion in bank credit, then
monetary policy should have a role to "lean against the wind". In this case also, credit growth may be an endogenous process, and unless a central bank has at its
disposal the authority to directly alter the flow of credit to a specific sector, it may have to resort to the interest rate instrument. The policy of using a macroeconomic tool such as interest rate to address a problem specific to a particular sector may not be appropriate, as it may have adverse consequences for other sectors. In India, however, the Reserve Bank has used in the past its sector specific prudential credit
policy measures. Hence, if credit is seen as a causative factor behind the build up of asset prices, the prudential regulatory policies can limit the credit flow and
"The bank-lending channel is particularly relevant for developing and emerging markets, given their underdeveloped financial markets where interest rates may not move to clear the market.
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Monetary Policy and Asset Price Interactions in India 1 77
Table 2. Causal relationship between changes in bank credit to private sector and changes in stock prices in India.
Null Hypothesis: F-Statistic Prob.
Changes in bank credit to private sector do not Granger cause changes . 0<2 n , j.oJ 0<2 n U.UUJ in stock , prices Changes in stock prices do not Granger cause changes in credit to ^ ̂ ^ ̂ private sector
discourage banks' excessive exposure to specific assets/sectors. Stock price cycles in India appear to exhibit a synchronised movement with credit cycles, although the lead and lag relationships between them change over different phases of the
cycle The Granger causality test between bank credit growth and changes in stock
prices in India for the period 1996:Q1 to 2010:Q1 provides evidence of significant bi-directional causal relationship between them, as presented in Table 2. This
implies that both credit boom and asset price booms reinforce each other - which
is the typical feedback loop between credit and asset prices. This two-way causation could emanate from the fact that credit growth may directly finance
purchases of stocks (which is limited in India) or indirectly push up asset prices by
financing real estate activities, enhancing thereby the prospects of future earnings. As the value of stocks increases, the capacity to borrow against the shares as
collateral also increases. This, however, is possible only to a limited extent in India.
B. Monetary policy and housing price dynamics
Housing wealth is considered to be an important component of the total
household wealth and is regarded critical to explaining the demand behaviour in
the advanced economies during the business cycles. Realisation of the asset
appreciation through refinancing of mortgage makes the demand impact
particularly strong, unlike in India where such refinancing of mortgage is mostly absent. As supply of housing is relatively inelastic in the short run, demand
pressures may lead to disproportionate increase in prices. Further, speculative demand in a situation of inelastic short run supply may lead to build up of bubbles.
An important link from monetary policy to asset prices is through the interest rate, which can influence the cost of mortgage debt and the demand for housing credit.10
10In advanced economies such as Japan, property prices were historically significantly responsive to real interest rate changes.
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178 Bhupal Singh and Sitikantha Pattanaik
Figure 1. Movement of stock prices and revenues from duties on housing in India.
50 -| - 90
1
; :
1
0 H 1 1 1 1 1 1 1 « 1 1 1 « 1 1 1 1 1 1 r -50 cMm*3-Ln<x>r»oo<T>o<- ic'ico'çj-Ln<*Dr**>.oo(X>o cy»cr>«y>cr>cr><r>cr>cr>oooooooooo»H œcjïOïcr>cr>cncncr>ooooooooooo fHrH*-lTH<-lr-lr-l*HrMfMCgrMr>JCgrMfMCMrNrM
Growth of Stamp duty and registration feesofthe States Average growth of Sensex (right scale)
The changes in interest rates also signal possible changes in valuation of assets.
Monetary policy is considered to influence the long-term cost of borrowing, which
is relevant for the debt-financed housing demand. A tightening of interest rates
may raise the cost of borrowing for households to finance such contractual debt
and hence may lead to a decline in the demand, which in turn could lead to a
downward pressure on prices. Given the lack of data on housing wealth in India and the absence of a
reasonable time series data even on housing prices, the house price behaviour has
to be studied using a number of proxy indicators.11 Stamp duties and registration fees collected by the State governments could shed some light on the house price behaviour in India because these should move in tandem with house price.12 As
1 'Housing wealth data for India are not available. On housing prices, which could trace the changes in the housing wealth, time series data are not available. The National Housing Bank (NHB) provides data on NHB Residential Index starting from 2008 but these data have two limitations: first, the data are available with only half yearly frequency and come with a significant time lag, second, the indices are provided only for a number of major cities and no all India index is computed. The Reserve Bank of India has also started compiling house price index recently. However, the index is available only since the second quarter of 2003 and is compiled only for Mumbai, which has been extended to few more cities since 2009. Thus, there is a lack of time series data on an aggregate housing price index for India.
12It could be argued that registration fees may not reflect the true movement in house price as the actual market value of the house could be understated with a view to partly avoid the stamp duties and registration fees. For empirical analysis, given the data constraints, one could assume that the extent of under reporting of the market value of the residential properties for registration purposes has a systematic pattern over time and thus, could still capture the broad trends in residential property prices.
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Monetary Policy and Asset Price Interactions in India 1 79
Figure 2. (B) Movement of Mumbai House Price Index.
300 280 - /
2 260 ' / 2 - 240 - / S 200 / ' J
120 " 100 I T. <N - -r ci <N - - ooqooqqqqo:
ooocooooo - cooooocooo <N<N<N<NfN<NfN<N<Nr)
evident from Fig. 1, the movement of stock prices and revenues from stamp duties
and registration fees on housing tend to follow a systematic relationship; they seem
to suggest a broad underlying asset price cycle with occasional deviations across
asset class. The recent boom-bust cycle in asset prices in India is evident from the
inverted U-shape pattern for the period 2003 to 2010.
Equity prices of the real estate firms listed in the stock exchanges also provide some information about the price behaviour in the housing sector. The stock prices of the realty sector attained a peak at the end of 2007 and there was a substantial
collapse following the financial market shocks from the global financial crisis (Fig.
2a). Although the broader index of stock prices (BSE Sensex) has returned closer to
the pre-crisis level, the realty stock prices tend to remain sluggish. This recent
behaviour of the realty sector stock price index seems to lag behind the extent of
increase seen in the National Housing Bank and RBI housing prices indices (Fig. 2b). Growth in bank credit to the construction sector (proxy for real estate) in India
exhibited a clear cyclical pattern during the period 2000-01 to 2009-10 (Fig. 3).
Figure 2. (a) Price movement of realty sector in India.
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1 80 Bhupal Singh and Sitikantha Pattanaik
Figure 3. Bank credit to construction sector in India.
-10 OtH(Nro^in<i>r>.oocr>OtHrMro^tinvor^ooa»o cr>cncnaicT>cr>(r>CT>cr>cr>ooooooooooTH cncx>cr><x>cr>cr>cr>cr>cr>cr>ooooooooooo *H t- I tH tH t- I r- I tH *H tH t-H OJ CM CNl fNj C'| f"sj fN fN Pvl fN CSl
Growth In gross bank credit to construction sector Growth in gross bank credit to industry
Reflecting the house price boom, growth in bank credit to the construction sector
was significantly above the overall growth of bank credit to industry. It may, however, be mentioned that as part of prudential regulations in India, bank credit to
sectors such as real estate and stock markets is regulated in relation to expansion in
the banks' overall asset portfolio. Secondly, the banks' credit exposures to real
estate and stock markets attract higher capital requirements.13 In respect of
residential housing, however, credit is given preferential treatment in terms its
classification as a priority sector loan including lower capital requirements. In a
situation where housing asset values tend to witness a secular growth, banks may have an incentive to expand credit to residential housing segment where credit
risks are perceived to be relatively low since such loans are backed by collaterals
whose values are expected to rise in future.
l3Risk weight on banks' exposure to the commercial real estate (CRE) and capital market were increased from 100 per cent to 125 per cent in July 2005. Given the continued rapid expansion in credit to the commercial real estate sector, the risk weight on exposure to this sector was increased to 150 per cent in May 2006. The general provisioning requirement on standard advances in specific sectors, i.e., personal loans, loans and advances qualifying as capital market exposures, residential housing loans beyond Rs.20 lakh and commercial real estate loans was also increased from 0.4 per cent to one per cent in April 2006 and further to two per cent on January 3 1 , 2007. These norms were relaxed to deal with the slowdown i growth that resulted from the global financial crisis. In October 2010, these norms were tightened again in response to rising asset prices.
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Monetary Policy and Asset Price Interactions in India 1 8 1
Table 2. Causal relationship between housing loans and interest rates.
Null Hypothesis: F-Statistic Prob
TB91 does not Granger cause dLBC hsg 3.01 0.06 dLBChsg does not Granger cause TB9 1 0.40 0.67 lOyGsec does not Granger cause dLBC hsg 2.93 0.00 dLBC hsg does not Granger cause lOyGsec 0.48 0.90
Another important dimension of the role of monetary policy in affecting house
prices is the impact of interest rate on the demand for bank credit by the housing sector, which in turn, affects house prices with a lag. The Granger causality test for
the period 2002:4 to 2010:6 suggests that short-term interest rate (TB91) Granger cause changes in bank credit to the housing sector (dLBC hsg) (Table 2). A
significant unidirectional causality is also observed from the long-term interest
rates (lOyGsec) to the demand for credit to the housing sector, though with longer
lags. The Granger causality analysis between house prices for the period 2003 :Q2 to
2010:Q2, proxied by housing prices for the Mumbai city (dLHPI), stock prices
(dLSENSEX_SA) and short-term interest rates measured by the weighted average call money rates (RCALL) provides some insights about the asset price dynamics
(Table 3). Interest rate changes seem to Granger cause changes in house prices. This finding may be relevant from the viewpoint of effectiveness of monetary
policy in influencing house prices in India. While asset prices may respond to
changes in interest rates, the policy interest rates would have been changed in
response to assessment about the growth and inflation outlook. Constructing a
counterfactual to study the impact of monetary policy changes on asset prices, thus, could be extremely difficult. This is primarily the reason as to why the Reserve
Bank has abstained from using interest rate instrument with the sole aim of
influencing asset prices. Although Joshi (2006) found that housing prices in India
are significantly much more sensitive to interest rate changes than to credit supply,
Table 3. Causal relationship between house prices, stock prices and short-term interest rate.
Null Hypothesis: F-Statistic Prob.
d(LSENSEX_SA) does not Granger Cause d(LHPI) 0.62 0.55 d(LHPI) does not Granger Cause d(LSENSEX_SA) 7.66 0.00 RCALL does not Granger Cause d(LHPI) 3.3 1 0.05 d(LHPI) does not Granger Cause RCALL 0.41 0.67
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1 82 Bhupal Singh and Sitikantha Pattanaik
the findings were based on a relatively short sample.
C. Empirical results from SVAR model
To examine the dynamic interactions among all the macroeconomic variables and asset prices, a structural vector auto regression (SVAR) model was estimated
using the following variables: real income (GDP), price level (WPI), real interest rate (call money rates minus GDP deflator), real bank credit (stock of non-food bank credit deflated by GDP deflator), real stock prices (Sensex deflated by GDP
deflator), and real exchange rate (6-currency REER index). The Gibbs sampling technique was applied to the VAR model, with standard Minnesota priors. The
priors are particularly useful to estimate models where the sample period in not
adequately long. The standard structural system can be considered of the following linear and stochastic dynamic form:
A0y, = B(L)yt.j + e, with i = 1, n (1)
The following theoretically plausible restrictions are imposed on the structure of the model to identify various structural shocks.
ey ' 1 o 0 0 0 o] £y
eP «21 1 0 0 0 0 Sp
er = 0 a32 1 0 0 a36 = er
ec «41 «42 «43 1 0 0 ec
es «51 a52 «53 «54 10 gs
gx «61 cc62 «63 a64 a65 1 e
The model has the standard assumption that real income shocks are most
exogenous and are not instantaneously affected by other macroeconomic
aggregates in the model, therefore, all coefficients in the matrix are restricted to zero. Price behaviour is impacted by the aggregate demand shocks contemporaneously but not by other shocks. The monetary policy reaction function has the restriction that
monetary policy does not contemporaneously respond to output shocks. This restriction is based on the argument that often the information on output is available to monetary authorities with a time lag. The reaction function, however, assumes contemporaneous reaction of monetary policy to price changes and the
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Monetary Policy and Asset Price Interactions in India 1 83
exchange rate movements. Exchange rate enters the monetary policy reaction
function as the central bank also attempts to maintain stability of foreign exchange market - a typical emerging market phenomenon. An important dimension of the
asset price dynamics captured in this model is the feedback between bank credit
and asset prices. Credit demand is contemporaneously affected by the real income
shocks, supply shocks and the monetary policy shocks.
Asset prices, measured in terms of stock market prices, are contemporaneously affected by the fundamental as well as the non-fundamental factors, except the
exchange rate. Asset price is contemporaneously affected by the credit shocks in
Figure 4. Impulse responses of stock prices to various shocks.
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1 84 Bhupal Singh and Sitikantha Pattanaik
the model as the underlying dynamics is that most asset price bubbles are
associated with excessive credit growth. The standard practice in the VAR literature on monetary policy and exchange rate interaction is to place the exchange rate last in the ordering while the exchange rate is allowed to react simultaneously to all shocks. The exchange rate can react instantaneously to all shocks, even
though the presence of nominal rigidities may lead to only gradual pass through of
exchange rate shocks to macroeconomic variables. This should provide enough restriction to identify the system, thereby allowing for the use of the non-recursive
decomposition. The model is now uniquely identified and the shocks are orthogonal
(uncorrelated). Quarterly seasonally adjusted data from 1996:Q2 to 20010:Q2 are used. Although some variables appear to be non-stationary, the VAR model is estimated in levels following Sims et al. (1990) that a VAR model in levels may incur some loss in estimators' efficiency but not the consistency. The objective of
estimating a VAR model in levels is to examine the relationship among variables. The optimal lag length based on various criteria (viz., LR test statistic, Akaike information criterion, Schwarz information criterion and Hannan-Quinn information
criterion) appeared to be three quarters. The estimated structural VAR model explains various channels through which
asset prices may be influenced, which are presented in Fig. 4. Aggregate demand shocks (i.e., an increase in aggregate demand) lead to an increase in stock prices in the short run and the impact fizzles out in the medium to long run. Favourable
aggregate demand shocks signal an improvement in the fundamentals of the
economy and raise expectations of the future earnings growth in the stock market. An adverse supply shock that causes sudden changes in relative prices, leads to
significant moderation in stock prices in the short to medium run. The asset price channel of monetaiy policy is found to be strong. A monetary policy shock causes
significant fluctuations in equity prices. Monetaiy policy works with variable lags. The impulse response functions exhibit that monetary policy tightening leads to a slow but significant moderation in stock price changes over the medium to long run. In the framework of the life cycle hypothesis of consumption, when stock
prices decrease, consumers' wealth also decreases and they spend less on
consumption. Thus, monetary policy could affect demand through the asset price channel. In India, on an average about 6 per cent of total financial assets of households are held in the form of equity.
An important issue of concern to the policy makers is how asset price shocks
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Monetary Policy and Asset Price Interactions in India 1 85
propagate to the rest of the economy and with what lags they impact various
macroeconomic aggregates. The estimated structural VAR model exhibits that
stock price shocks affect output with some lag over the medium-term, though with
no significant long run impact (Appendix 1). The impact on output could be
through the typical wealth effect and balance sheet channels that cause changes in
consumption and investment. An adverse output shock, which may be the result of
negative shock to asset prices, triggers an expansionary monetary policy response in terms of lower interest rate in the short run. This corroborates the indirect role of
monetary policy relative to asset prices, i.e., through the impact on output. Asset
price shocks do not seem have a significant direct impact on the price level. Shocks
from stock prices explain only marginal fluctuations in the overall price level over
medium to long run. This suggests no need for even indirect monetary policy
response to asset price developments, unlike the impact observed through output. Stock price shocks also do not seem to lead to any noticeable changes in interest
rates in the short run. It suggests that monetary policy does not respond to asset
prices. This could also be because of the muted impact of stock price shocks on
inflation. Favourable stock price shocks tend to cause increase in the demand for
bank credit with a lag over the medium-term. In fact, by the end of eight quarters, stock price shocks explain about 10 per cent of the fluctuations in real demand for
credit. The most significant impact of stock price shocks is on the real exchange rate, which possibly works through changes in capital flows. Higher stock prices
change the return differentials for foreign investors, making investment in the
Indian markets more attractive, which in turn lead to higher inflows and hence
appreciation of the real exchange rate in the short run. This effect, however, moderates over medium to long run.
The above findings suggest that though the direct impact of asset price shocks
on goods prices is not significant, they may still be of interest to the central bank
from the standpoint of their impact on credit demand, output and the exchange rate.
Thus, monetary policy may respond to asset prices only indirectly, for which,
however, clearer identification of the influence of asset price changes on inflation,
growth or exchange rate would be important. Asset prices appearing to be sensitive
to monetary policy changes do not provide a strong case for deploying monetary
policy to counter asset price movements. Relying on the asset price channel to
achieve the ultimate policy goals of growth and price stability could be too risky a
proposition to be ventured. Thus, interest rate channel should remain the prime focus of monetary policy, even if asset prices may respond to changes in monetary
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1 86 Bhupal Singh and Sitikantha Pattanaik
policy, which in turn may influence the ultimate goal variables that the monetary
policy aims to achieve. Asset prices as such should not become an intermediate
objective of monetary policy. The response of stock prices to credit market shocks validates the presumed role
of credit expansion in contributing to the asset price bubbles.14 A comparative assessment of the impulse response functions reveals that monetary policy
tightening leads to a moderation in credit demand over the medium-term, given the usual lags in the impact of monetary policy (Appendix 1). The tightening of policy interest rates, thus, impacts the stock prices, as financing the leverage in the markets turns costlier.15 The impulse responses exhibit that a positive shock to bank credit causes significant increase in equity prices over medium to long run. The credit market shock at the same time causes significant variations in real
output. Thus, the asset price dynamics becomes complicated as the positive credit shocks lead to simultaneous increase in both output and asset prices. From the
perspective of a monetaiy policy response, it becomes difficult to segregate the part of asset price increase that may be caused by improvement in fundamentals from that led by speculative credit flows to asset markets.
The stock market shock, measured in terms of lagged impact of the stock prices, could reflect composite impact of backward-looking investor behaviour, overreaction by agents to news about the fundamentals, impact of sudden surges in
portfolio inflows and the herd behaviour/animal spirits. These shocks are most dominant in causing fluctuations in stock prices in the short run but their impact peters-off at a rapid pace. Another important channel through which asset prices are impacted is the exchange rate channel. A positive shock to real exchange rate,
signifying the adverse external competitiveness shock, results in significant moderation in stock prices with a lag, consistent with lags in exchange rate transmission to macroeconomic aggregates. The impact, however, does not seem to be persistent.
The results of the decomposition of fluctuations in stock prices caused by
1 Variations in bank credit are an important channel of monetaiy policy transmission mechanism even for central banks that rely on interest rates to convey their policy stance. Modulations in policy interest rates by the central bank influence credit market conditions which reinforce the effects of the traditional interest rate channel of monetary transmission. The impact of credit channel on asset prices can also work through changes in market perception. As credit conditions are tightened, the perception about the overheating of the economy may get strengthened and accordingly the stock prices would be adversely affected.
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Monetary Policy and Asset Price Interactions in India 1 87
Table 4. Decomposition of fluctuation caused in stock prices. (%) _ Demand Supply Monetary Credit market Asset price Exchange
shock shock policy shock shock shock rate shock
1 14.1 0.0 1.1 0.5 84.3 0.0 4 10.4 26.9 6.4 2.1 52.4 1.8 8 6.1 13.3 8.4 18.8 27.0 26.5 12 7.3 13.4 14.9 21.5 20.6 22.2 16 7.4 14.3 14.1 23.8 18.4 22.0 20 7.7 15.3 13.6 24.4 17.8 21.2
various macroeconomic shocks are presented in Table 4. Although the asset price shock explains the predominant part of variations in stock prices in the short run, it
is the credit demand shock that explains the largest proportion of variations in asset
prices over the medium to long run. The aggregate demand and supply shocks tend
to have short to medium-term impact on stock prices. The variance decomposition
analysis of fluctuations in credit demand also reveals that aggregate demand shocks
explain significant variation in real credit demand, which in turn, might be
impacting on the stock price movements given the causal relationship between
bank credit and stock prices (Appendix 2). The real exchange rate shock turns
significant over the medium to long run in explaining fluctuations in stock prices in
India. The role of exchange rate in affecting asset prices could emanate from
Figure 6. Historical decomposition of fluctuations in real stock prices explained by various macroeconomic shocks.
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1 88 Bhupal Singh and Sitikantha Pattanaik
changes in relative attractiveness of returns to foreign capital in the stock markets in the short run due to nominal appreciation of the rupee and a loss of overall external competitiveness over the medium to long run, which may adversely affect
the growth outlook and hence dampen stock prices. The contributions of various shocks to asset price movement in India could be
gleaned from the historical decomposition of the fluctuations in stock prices. It is
evident from Fig. 6 that booms in stock prices since the mid-2000s were, on an
average, dominated by real credit and stock market shocks. The stock market residual shocks capture the composite impact of a host of factors including the
news about fundamentals and sudden changes in the market sentiments driven by foreign institutional investors as well as the unanticipated domestic shocks.
Although the contribution of the monetary policy shocks during the early phase of the recent asset cycle boom appeared to be significant, it tapered-off subsequently.
IV. Conclusion
In the post-global crisis period there has been an increasing emphasis on the need to explore the scope of monetary policy responding directly to asset price developments to be able to promote financial stability. This renewed interest in the role of monetary policy in stabilising asset price cycles has compelled policy makers to have a re-look at the pre-crisis consensus that seemed to favour a hands- off approach to asset price but manage the consequences of both booms and busts in asset price cycles. The extensive debate after the global crisis does not seem to
suggest that the pre-crisis consensus was blatantly fallacious. Alternative instruments at the disposal of central bank, namely micro and macro-prudential tools, could be superior relative to the interest rate instrument, both in terms of effectiveness and minimising the overall costs for the economy. Monetary policy as a macroeconomic policy tool can ensure an environment in which prudential regulation could become somewhat more effective.
In India, despite the limited risks from asset price cycles to macro-financial conditions relative to the advanced economies, much greater reference to asset
prices is being made in the context of monetary policy. The concerns relating to
surges in capital flows fuelling asset prices has also provided another dimension to the debate on the dynamics between capital flows, asset prices and monetary policy. The Reserve Bank has used in the past both micro and macro-prudential measures to limit the risks to financial stability from asset price cycles. It, however,
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Monetary Policy and Asset Price Interactions in India 1 89
has justifiably refrained from using policy interest rates with the specific intention of influencing asset prices. This paper provides empirical evidence to explain the
appropriateness of such an approach and highlights that the same approach may have to continue. Expected impact of asset price trends on inflation and output, however, needs to be assessed regularly so that the scope for indirect response of
monetary policy to asset price shocks could be integrated to the monetary policy framework. The macroeconomic analysis for the conduct of monetary policy may be relevant for designing the structure and even for deciding on the timing of
macro-prudential measures, but the monetary policy itself, which already caters to
multiple objectives, should not be assigned any explicit direct role to stabilise asset
prices. In this context, any policy that aims at limiting the overall pace of credit
growth may have to be driven by developments such as either economic
overheating or persistent high inflation, but not the perception of an asset price bubble. Similarly, if an accommodative monetary policy stance has to be sustained for a prolonged period in response to an economic slowdown or a recession, the fear of such a stance leading to asset price inflation should not trigger hasty tightening of monetary policy. For the purpose of clarity, sector specific limits on the flow of credit to asset price sensitive sectors, or even caps on direct and indirect
exposure of the banking system to asset price cycles should be seen purely as
prudential measures, which are different from monetary policy measures. The empirical analysis for India exhibits that while interest rate changes cause
changes in stock prices, the reverse causality does not hold. This validates the point that monetary policy in India does not respond to asset prices, but the asset price channel of monetary policy exits. Evidence of a significant bi-directional causal
relationship between credit growth and asset price trends does not provide any
unambiguous result about the role of credit in asset price bubbles. This is so
because of the role of a common factor; i.e. strong GDP/IIP growth coinciding with high credit growth, and the former driving the asset prices up.
Regarding housing assets, given the absence of a reasonably long time series data on house prices, this paper used a number of proxy variables. The movement
of stock prices and collection of "stamp duties and registration fees" relating to
housing tend to follow a symmetric relationship, indicating the possibility of a
broad-based asset price cycle. The housing credit demand in India appears to be
sensitive to interest rate movements, which though does not validate an explicit role for monetary policy in influencing housing prices. This is because the impulse
response functions reveal that monetary policy tightening leads to a moderation in
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1 90 Bhupal Singh and Sitikantha Pattanaik
credit demand over the medium-term, given the usual lags in the impact of
monetary policy, which in turn gives rise to lower real output. Thus, any asset price objective attempted to be achieved through monetary policy actions would involve sacrifice of growth. Given the possibility of an adverse feedback loop, where
falling asset prices and contraction in output could intensify in a spiral, direct use of monetary policy may better be avoided. Moreover, asset price dynamics could
be difficult to decipher for meaningful use in the conduct of monetary policy. For
example, an increase in the flow of credit in the VAR model seems to lead to increase in both output and asset prices. It could be, however, particularly difficult to segregate the part of asset prices increase that might have been caused by improvement in fundamentals from the part led by speculative credit flows to asset markets. This ambiguity suggests why countercyclical regulatory policies to counter asset price bubbles could be more appropriate relative to direct use of
monetary policy.
Received 18 November 2010, Revised 12 February 2012, Accepted 14 February 2012
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Monetary Policy and Asset Price Interactions in India 193
Appendix
Appendix 1. Impulse response of macroeconomic variables to various shocks.
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1 94 Bhupal Singh and Sitikantha Pattanaik
Appendix 2. Decomposition of fluctuation caused in various macroeconomic variables (%). _ Demand Supply Monetary Credit market Asset price Exchange
shock shock policy shock shock shock rate shock
Aggregate output 1 100.0 0.0 0.0 0.0 0.0 0.0 4 71.3 3.4 1.6 1.9 14.3 7.5 8 46.5 12.2 1.1 18.6 11.2 10.3 12 38.5 22.4 1.5 22.4 9.7 5.5 16 36.0 25.5 1.1 25.6 7.9 3.9 20 34.5 30.0 0.8 24.8 6.9 3.0
Price level 1 1.2 98.8 0.0 0.0 0.0 0.0 4 9.5 81.4 7.7 0.2 1.1 0.1 8 14.8 72.6 9.0 1.0 1.3 1.3 12 19.2 66.0 7.9 2.8 2.4 1.6 16 21.3 62.1 6.4 5.4 3.0 1.7 20 24.1 57.4 5.4 8.2 3.4 1.6
Real short-term interest rate 1 0.0 10.4 89.6 0.0 0.0 0.0 4 2.5 19.0 73.6 0.6 1.5 2.8 8 1.9 27.9 56.0 3.8 5.2 5.2 12 2.1 31.1 47.7 3.4 4.8 11.0 16 2.1 31.6 45.5 3.8 4.6 12.4 20 2.2 31.8 44.9 3.8 4.6 12.7
Real bank credit 1 5.0 8.2 1.2 85.6 0.0 0.0 4 20.1 5.1 5.4 61.8 7.0 0.8 8 23.1 16.8 5.9 43.2 10.4 0.7 12 24.2 18.4 4.5 43.2 8.0 1.6 16 24.6 25.3 3.6 38.1 6.8 1.6 20 25.4 27.5 3.3 36.1 6.2 1.5
Real exchange rate 1 0.7 1.8 3.8 2.0 14.2 77.5 4 0.5 2.3 4.9 2.2 19.4 70.7 8 1.2 7.3 3.2 14.4 11.7 62.2 12 2.0 13.4 7.1 12.8 10.3 54.5 16 1.9 13.7 7.0 13.3 10.1 54.1 20 2.1 14.1 6.9 13.6 10.0 53.3
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- Article Contents
- p. [167]
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- Issue Table of Contents
- Journal of Economic Integration, Vol. 27, No. 1 (March 2012), pp. 1-205
- Front Matter
- Sequencing Asian Regionalism: Theory and Lessons from Europe [pp. 1-32]
- Is the Eurozone Rescue Strategy Tantamount to the Rearrangement of the Deckchairs on the Titanic? [pp. 33-79]
- Regional Integration and Real Convergence: Evidence from MENA Countries [pp. 80-114]
- Stock Market Integration Between Three CEECs [pp. 115-122]
- Revisiting the Apparent Paradox: Foreign Capital Inflow, Welfare Amelioration and 'Jobless Growth' with Agricultural Dualism and Non-traded Intermediate Input [pp. 123-133]
- Testing for "Contagion" of the Subprime Crisis on the Middle East and North African Stock Markets: A Markov Switching EGARCH Approach [pp. 134-166]
- Monetary Policy and Asset Price Interactions in India: Should Financial Stability Concerns from Asset Prices be Addressed Through Monetary Policy? [pp. 167-194]
- Does Input Substitutability in Banking Differ across Accession and Non-Accession Countries in Central and Eastern Europe? [pp. 195-205]
- Back Matter
Monetary policy and financial stability empirical evidence.pdf
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Monetary policy and financial stability: empirical evidence from Central and Eastern European countries Vasile Cocrişa & Anca Elena Nucub a Professor, Alexandru Ioan Cuza University of Iasi, Faculty of Economics and Business Administration, B-dul Carol 1 nr.22, Iasi, 700505, Romania, e-mail: b PhD Candidate, Alexandru Ioan Cuza University of Iasi, Faculty of Economics and Business Administration, B-dul Carol 1 nr.22, Iasi, 700505, Romania, e-mail: Published online: 03 Jun 2014.
To cite this article: Vasile Cocriş & Anca Elena Nucu (2013) Monetary policy and financial stability: empirical evidence from Central and Eastern European countries, Baltic Journal of Economics, 13:1, 75-98, DOI: 10.1080/1406099X.2013.10840527
To link to this article: http://dx.doi.org/10.1080/1406099X.2013.10840527
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Monetary policy and financial stability: empirical evidence from Central and Eastern European countries
Vasile Cocriş1 and Anca Elena Nucu2
Abstract
The international financial and economic crisis highlights that central banks should go be- yond their traditional emphasis on low inflation to adopt an explicit goal of financial stability. Our paper addresses this highly topical issue of macro-prudential framework with the focus on effectiveness of monetary policy in affecting some financial stability indicators, in the experience of several Central and Eastern European countries during 2003M01-2012M06. Using a Structural Vector Autoregressive model and impulse response function, we analyze the impact of short-term interest rates upon industrial production, loan to deposit ratio for the banking system, stock prices and exchange rate (proxy variables for financial stability). We want to test if the interest rate is conducive to financial stability. Our empirical results show that the effectiveness of the short-term interest rate in affecting selected asset prices depends on monetary policy strategy. In the case of the Czech Republic, Hungary, Poland and Roma- nia, the interest rate instrument used for inflation targeting is conducive to financial stability. Among countries with a fixed exchange rate regime, only in Bulgaria does transmission of the foreign interest rate impulse to domestic variables promote financial stability. Additionally, our results show that in Latvia and Lithuania adjustments to the monetary policy of the Euro- pean Central Bank (ECB) are not in accordance with country-specific conditions. The paper contributes to a policy debate on the design of macro-prudential polices in the aftermath of the boom-bust cycle experienced by the Central and Eastern European countries in the second half of the last decade.
JEL classification codes:: E52, C58, G01 Key words: monetary policy, financial stability, Structural Vector Autoregressive model, CEE countries
1. Introduction
It has long been understood that monetary policy can enhance financial stability (IMF, 2012), but the international financial and economic crisis highlights that central banks should go beyond their traditional emphasis on low inflation and adopt an explicit goal of financial sta- bility. Our paper addresses this highly topical issue of macro-prudential framework with the focus on effectiveness of short-term interest rates in affecting selected asset prices.
1 Professor, Alexandru Ioan Cuza University of Iasi, Faculty of Economics and Business Administration, B-dul Carol 1 nr.22, Iasi, 700505, Romania, e-mail: [email protected] 2 PhD Candidate, Alexandru Ioan Cuza University of Iasi, Faculty of Economics and Business Administration, B-dul Carol 1 nr.22, Iasi, 700505, Romania, e-mail: [email protected]
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The purpose of our paper is to investigate the implications of monetary policy on financial stability in the experience of several Central and Eastern European (CEE) countries, during 2003M01-2012M06. Using a Structural Vector Autoregressive model, we analyze the impact of the short term interest rate upon industrial production, loan to deposit ratio for the banking system, stock prices and exchange rate (proxy variables for financial stability). We want to test whether a monetary policy interest rate is conducive to financial stability.
The literature outlines that there is no widely accepted definition of financial stability or a standard measurement framework. As in Granville and Mallick (2009), we define financial stability in terms of changes in share prices, the exchange rate measured as local currency versus the single European currency and the bank loan-deposit ratio. We also examine the effect of monetary policy on the real sector, by including the industrial production index in the empirical model.
The motivation to address these issues is related to a niche revealed by the literature review. Although the monetary policy transmission mechanism in the candidate countries has been written about from the empirical standpoint, the studies are less numerous, and the results of- ten contradictory due to the relatively short time series and the narrow set of variables. Thus, we aim to address this problem by considering different data series, extending the sampling and grouping the countries according to their monetary policy strategy. In addition, from the econometrical standpoint, the period under review represents a real challenge because we are dealing with structural breaks of the time series due to the macroeconomic impact of the crisis since 2007.
The paper is organized as follows. The next section briefly surveys the major contributions of the literature review. Section 3 lays out the data and the methodology used. Section 4 evalu- ates the empirical results. Section 5 concludes.
2. Literature review
Interest in analysis of the monetary policy transmission mechanism has increased in the last decade and the Vector Autoregressive (VAR) approach proposed by Sims (1980) has been extensively used in empirical research. The academic literature abounds in studies which analyze the impact of monetary policy on macroeconomic variables in the United States, Great Britain and the euro area using Vector Autoregressive methodology in its different variants (Structural Vector Autoregressive-SVAR, Vector Error Correction-VEC, Structural Vector Error Correction- SVEC) and impulse response analysis derived from these. Among the studies carried out on the example of Central and Eastern European countries, we recall those of Ganev et al. (2002), Elbourne and de Haan (2006), Coricelli, Egbert & MacDonald (2006) Anzuini and Levy (2007), Minea and Rault (2008), Gavin and Kemme (2009), Jaro- cinski (2010), Minea and Rault (2011), Pirovano (2011), Spulbăr et al. (2012). The scarcity of studies is related to the difficulty of using econometrics for emerging countries. The possible causes could be:
• Lack of long data series. Performing an empirical analysis requires a large number of observations, with some frequency in order to draw conclusions. Currently, we are deal- ing with structural breaks in time series due to the macroeconomic impact of the crisis.
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• Lack of comparability between data series on samples of countries. • Administrative control of economic variables such as prices or interest rates. This takes into consideration that economic variables which are controlled by the authorities gener- ate misleading results because empirical models “assume that the variables of interest are random” (see, for example, Botel, 2002).
Ganev et al. (2002), using Granger causality and impulse response analysis, on the example of CEE countries, find evidence that the exchange rate channel is stronger and more stable than the interest rate channel. Anzuini and Levy (2007) examine, empirically, the effects of monetary policy shocks in the Czech Republic, Hungary and Poland, using a Vector Autore- gressive (VAR) model. Their results state that in all countries macroeconomic variables react in line with economic theory: an increase by one percentage point in the interest rate leads to a persistent and significant decline in industrial production, causes an appreciation in the exchange rate and a significant decline, after one year, of the consumer price index. Thus, Anzuini and Levy (2007) find no evidence of counter-intuitive effects of monetary policy shocks.
Elbourne and de Haan (2006), using the Structural VAR methodology, examine to what extent the monetary policy transmission mechanism is related to indicators of financial structure, in the experience of ten countries from Central and Eastern Europe. The variables under con- sideration (industrial production, consumer prices, exchange rates) react according to eco- nomic theory in all countries analyzed, but with differences in the magnitude of the impact and shock persistence. Unlike Anzuini and Levy (2007), Elbourne and de Haan (2006) find a counter-intuitive response: following an increase in industrial production due to monetary policy shock in Romania. The counter-intuitive results obtained for the candidate countries are due, mainly, to small VAR models, typically four variables (see, for example, Balabanov and Brüggemann, 2012).
Jarocinski (2010) performed a comparative impulse response analysis to monetary policy shocks on the example of the euro area countries before EMU (Finland, France, Italy, Portu- gal and Spain) and new EU member states in CEE (the Czech Republic, Hungary, Poland and Slovenia) and finds that responses of macroeconomic variables to monetary policy shocks in the new Member States are broadly similar to those in the euro area countries.
Spulbăr et al. (2012), using a Bayesian Vector Autoregressive Model on Romanian experi- ence over the past ten years reveal that the exchange rate remains an important mechanism which significantly affects real economic variables and “output puzzle” and “price puzzle” effects do not appear after a positive interest rate shock.
The presence of a particular monetary system in Bulgaria has attracted the attention of re- searchers. Minea and Rault (2008), using estimations based on the SVAR, analyze the impact of the European Central Bank (ECB) interest rate on four Bulgarian monetary aggregates and find that both the domestic interest rate and broad money M3 follow key interest rate dy- namics only in the medium and long term, therefore confirming the endogeneity of the main financial variables under the currency board. In a related line of research, the same authors, Minea and Rault (2011) assess the impact of the ECB and FED interest rate on Bulgarian monetary variables using generalized impulse response functions. They find that ECB mon-
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etary policy shocks are more rapidly absorbed and have a less significant impact on domestic variables compared with FED interest rate shocks.
Much less, however, has been written about the optimal monetary instrument to maintain financial stability. In the literature, this topic is currently at the centre of academic debate. Goodhart et al. (2011) assess the choice between adopting a monetary base or an interest rate setting instrument for prudential purposes. The authors suggest that the interest rate in- strument is preferable, since during times of panic or financial crisis the central bank auto- matically satisfies the increased demand for money. A recent strand of literature focuses on central banks’ practice of smoothing the interest-rate (Giorgio and Rotondi, 2011) in order to promote financial stability. The authors conclude that an interest rate smoothing policy can enhance financial stability, but also gives rise to indirect effects that lower financial stability (Smith and Egteren, 2005). To the best of our knowledge, none of these studies was con- ducted on the example of CEE countries.
In conclusion, as observed, the academic literature provides no consensus on the sign and size of responses by macroeconomic variables after a monetary policy shock in CEE countries. Also, the role of the interest rate in promoting financial stability is currently at the centre of academic debate.
3. Methodology and data
In order to analyze the role of interest rate policy in contributing to financial stability, we follow the standard literature and apply a Structural Vector Autoregressive model on the ex- perience of several CEE countries: Bulgaria, the Czech Republic, Hungary, Latvia, Lithuania, Poland and Romania. Therefore, we have chosen the states from Central and Eastern Europe which joined the EU in 2004 and 2007, but which are not members of the Euro Zone.
3.1. Methodology
Our point of departure is a K-dimensional stationary, stable VAR(p) process with the follow- ing form: Yt= ν+A1Yt-1+...ApYt-p+ut, (1)
where Yt is a (K*1) vector of endogenous variables, ν is a (K*1) vectors of intercepts, Ap are the (K*K) fixed VAR coefficient matrices and ut=(u1t,...,ukt)’ is an unobservable error term, with the usual properties: E[ut] = 0 (2)
E[utut ’]=∑u (time invariant variance-covariance matrix) (3)
E[utus] = 0, ∀t ≠s. (4) K is the number of variables.
Given the trending properties of the time series, we employ information criteria to select the lag length of the VAR, including a constant and a deterministic trend. We select the lag length
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according to the Akaike Info Criterion (AIC) and Final Prediction Error (FPE). Our analysis employs a reduced-form specification of the relationship between the variables, based on the sequential elimination algorithm- Top-Down (TD) procedure which starts from the last regressor in the equation and checks whether deleting it improves the criterion value and so on (Lutkepohl, 2004). For the VAR specifications, we conduct a series of diagnostic tests. We test against autocorrelation, nonnormality and ARCH effects in the VAR residuals.
Since the purpose of our empirical analysis is to evaluate the response of financial variables to a monetary policy shock, we explain the methodology of the impulse response analysis in the following. Monetary policy shock is the only shock identified here. The correlations of the error term may indicate that a shock in one variable is likely to be accompanied by a shock in another variable. Therefore, we assume that structural shocks are orthogonal, which means that the covariance matrix of the VAR residuals conveys information about the coefficients of the contemporaneous relationships between endogenous variables, as in Jarocinski (2010). The relationship between reduced-form disturbances ut and structural shocks εt is as follows: ut=B* εt, (5)
with the following structure in the case of the Czech Republic, Hungary, Poland, Romania:
where B is a lower triangular matrix obtained from a Cholesky decomposition of the covari- ance matrix ∑u, such that BB’=∑u. εirs and εLIBOR represent the monetary policy shock. The present model with ut=B* εt and εt ∼ (0, IK) is a B-model and K(K − 1)/2 restrictions have to be imposed to identify B. We obtain these restrictions from a “timing scheme” for the shocks. In this paper, we assume a recursive transmission scheme under the following two assump- tions:
• the industrial production index does not respond immediately to monetary policy shock; • a monetary policy shock may have an immediate impact on the loan to deposit ratio, index prices and exchange rate.
Restricting B to be a lower triangular matrix ensures that the first component of εt, ε1t, can have an instantaneous impact on all equations, where ε2t cannot affect the first equation in- stantaneously but only all the others, and so on. Hence, the recursive structure implies the required K(K-1)/2 zero restrictions.
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Taking into consideration that the effects of shocks are easily seen in terms of moving average representation: yt=Φ0ut+ Φ1ut-1+ Φ2ut-2+..., (6)
we obtain the following form: yt=ω0 εt+ ω1 εt-1+..., (7)
where ωi= ΦiB, ω0=B. ΦiB are the matrices of impulse response function.
3.2. Data
The short-term interest rate represents the instrument of monetary policy in our empirical research.
The economic and financial crisis has determined central banks to pay greater attention to financial stability because a stable financial system provides necessary conditions for robust implementation of an efficient monetary policy. Therefore, we have considered one proxy variable for major markets which conceal risks that may affect the stability of the domestic financial system, as follows:
• loan to deposit ratio as a proxy for the banking system; • stock index as a proxy for the capital market; • exchange rate measured by local currency versus the euro as a proxy for the foreign exchange market.
Industrial production is our proxy for economic growth.
The datasets used in the empirical analysis depend on the monetary policy strategy of the countries from the sample. Therefore, for the Czech Republic (CZ), Hungary (HU), Poland (PO) and Romania (RO), countries operating under an inflation targeting regime, we estimate a five-dimensional Structural Vector Autoregressive Model with: log of industrial production index, 3 months short term interest rate, loan to deposit ratio, log of stock prices and log of ex- change rate measured as local currency versus the euro. The loan to deposit ratio is computed as follows: Loans granted to clients (gross value) / Deposits from clients*100.
For Bulgaria (BG), Latvia (LV) and Lithuania (LT), countries operating under a fixed ex- change rate regime, we also estimate a four-dimensional Structural Vector Autoregressive Model with: log of industrial production index, 3 months EUR LIBOR interest rate, loan to deposit ratio for the banking system and log of stock prices. Taking into consideration that changes in Bulgarian, Latvian and Lithuanian monetary variables are non discretionary- decided, we consider that shocks come from the ECB refinancing interest rate. However, in line with other studies (see, for example, Minea and Rault, 2008) that emphasize the fact that changes in ECB interest rate are too rare to produce a sufficient amount of variability, we consider the 3 month LIBOR EUR interest rate as an exogenous variable. Moreover, figure 1 illustrates the evolution in accordance with LIBOR and the ECB refinancing interest rate during January 2003-June 2012.
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Figure 1 Evolution of 3 month LIBOR EUR interest rate and ECB refinancing interest rate (%), January 2003-June 2012
6
5
4
3
2
1
0
LIBOR EUR 3M
ECB refinancing interest rate (EA11-2000, EA12-2006, EA13-2007, EA15-2008, EA16-2000, EA17)
20 04
M 01
20 04
M 04
20 04
M 07
20 04
M 10
20 03
M 01
20 03
M 04
20 03
M 07
20 03
M 10
20 05
M 01
20 05
M 04
20 05
M 07
20 03
M 10
20 06
M 01
20 06
M 04
20 06
M 07
20 06
M 10
20 07
M 01
20 07
M 04
20 07
M 07
20 07
M 10
20 08
M 01
20 08
M 04
20 08
M 07
20 08
M 10
20 10
M 01
20 10
M 04
20 10
M 07
20 10
M 10
20 09
M 01
20 09
M 04
20 09
M 07
20 09
M 10
20 11
M 01
20 11
M 04
20 11
M 07
20 11
M 10
20 12
M 01
20 12
M 04
Source: Datastream Thomson Reuters
In addition, the currency board strategy implies that the exchange rate of BGN, LTL and LTV against the euro is constant, so that from an empirical standpoint the analysis has no coher- ent interpretation. Therefore, we dropped out the exchange rate from the VAR specification for Bulgaria, Latvia and Lithuania. Also, given the insignificant role of the domestic interest rate in the loan market (high euroisation) in these countries one may consider dropping the domestic interest rate from a VAR country.
In line with Jarocinski (2010), we have not included monetary aggregates in the baseline model. It is assumed that central banks target short-term interest rates and adjust monetary aggregates accordingly with this objective.
Monthly time series data ranging from 2003M01 to 2012M06 have been used, therefore giv- ing a total of 114 observations. The start of the estimation sample is governed by data avail- ability. All series are obtained from Datastream Thomson Reuters. The choice of frequency was motivated by the necessity for accurate estimates, but this requires use of industrial production instead of GDP per capita detrended, which is reported quarterly. We focus on monthly instead of quarterly frequency because the number of observations in the second case would simply not be enough to perform a structural analysis, as the error bands would be very large and results non-informative. We define the variables as follows: LIBOR_EUR_3M- 3 month LIBOR EUR interest rate, irs- short term interest rate, log_ip- log of industrial production index, ldr- loan to deposit ra- tio for the banking system, log_er- log of exchange rate measured as local currency per EUR, log_sp- log of stock prices.
We would like to deal with economies for which the exchange rate arrangements do not change in the estimation, because this fact represents an attempt to minimize the effects of parameter inconsistency that one would expect when estimating over multiple regimes (see, for example, Elbourne and de Haan, 2006). However, the Czech Republic and Hungary have modified the exchange rate regime in the period analyzed, according to the International
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Monetary Fund classification. Moreover, in less industrialized economies, it is not clearly specified how the exchange rate regime affects transmission of a monetary shock.
The current economic crisis could represent a structural break in data. Taking a look at the evolution of the time series, we observe the fact that the behavior of variables has changed since 2008, after Lehman Brothers’ bankruptcy. Moreover, Chow tests yield robust results concerning structural breaks. In order to check whether the structural analysis is still valid for the whole sample, we have compared impulse responses of different subsamples (i.e. 2003M01-2008M07, 2008M08-2012M06) and we find that the patterns remain unchanged. In line with other studies (see, for example, Gerke et al., 2008) we conclude that the whole sample remains adequate for empirical research.
4. Empirical results
The unit root analysis, according to Augmented Dickey-Fuller (ADF) and Philips-Perron tests, indicates that the unit root hypothesis cannot be rejected for all the time series consid- ered and that all of them can be characterized as integrated of the order of 1, I(1).
The AIC and FPE suggest two lagged differences for the Czech Republic, Hungary, Poland, Romania and Bulgaria, and respectively, three lagged differences for Latvia and Lithuania.
We present the country impulse response functions in the order of country grouped by the degree of nominal exchange rate flexibility.
Figure 2 plots the responses of financial variables in the Czech Republic to a monetary policy shock. Our empirical results show that after a monetary policy shock via the interest rate, all the variables react in line with economic theory: the industrial production index decreases by roughly 0.08%, after 8 months, the loan to deposit ratio declines and also stock prices drop down. All these effects are statistically significant and the shock has transitory effects, being absorbed after 40-50 periods ahead. In the short run, the local currency appreciates against the single European currency under the impact of a monetary policy shock, but this effect is not statistically significant. Anzuini and Levy (2007), applying a VAR model on the Czech example between July 1997 and January 2002, find that industrial production decreases and the nominal exchange rate measured as local currency versus the U.S. dollar appreciates after a monetary policy shock. The inverse relationship between the interest rate and industrial production is also confirmed by Jarocinsky (2010) and Elbourne and de Haan (2006). In line with our results, Pirovano (2010), using a SVAR model with short-term restrictions, finds that the stock index drops by 0017, after 8 months, under a restrictive monetary policy shock.
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Figure 2 Responses of financial variables in the Czech Republic to an interest rate shock together with a 95% Hall bootstrap confidence interval based on 1 000 replications Response of LOG_IP to IRS
0 5 10 15 20 25 30 35 40 45 50
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Response of IRS to IRS
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Response of LDR to IRS
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Response of LOG_SP to IRS
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Response of LOG_ER to IRS
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0 5 10 15 20 25 30 35 40 45 50
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-0.016
Note: Vertical axis - deviation from the baseline scenario, horizontal axis - number of months after the shock Source: own estimates based on JMulTi
In Figure 3, the responses of Hungarian macroeconomic variables to an interest rate shock are plotted. As in the case of the Czech Republic, the industrial production index follows a downward trend and the effect is statistically significant. Also, the central forecast for the loan to deposit ratio and stock prices is negative. In the short run, the national currency appreci- ates against the euro, but the error bands are again quite wide. The negative co-movement between the interest rate and the industrial production index is also confirmed by Jarocinski (2010) and Elbourne and de Haan (2006). Regarding evolution of the stock market index, our empirical results are in line with Pirovano’s study (2010) which confirms the negative rela- tion between this variable and the interest rate.
Figure 3 Responses of financial variables in Hungary to an interest rate shock together with a 95% Hall bootstrap confidence interval based on 1 000 replications
Response of LOG_IP to IRS
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Response of IRS to IRS
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Response of LDR to IRS
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Response of LOG_ER to IRS
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Note: Vertical axis - deviation from the baseline scenario, horizontal axis - number of months after the shock Source: own estimates based on JMulTi
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Figure 4 plots the responses of financial variables in Poland to a monetary policy shock. As we can see from the figure, under an unexpected increase in the short term interest rate, all the variables move in the expected direction: the industrial production index falls, the loan to de- posit ratio decreases, the Polish stock market index loses about 0.7%, and the local currency appreciates against the EUR in the short run. Our results are in line with those of Jarocinski (2010) and Pirovano (2010).
Figure 4 Responses of financial variables in Poland to an interest rate shock together with a 95% Hall bootstrap confidence interval based on 1 000 replications Response of LOG_IP to IRS
0 5 10 15 20 25 30 35 40 45 50
0.004
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Response of IRS to IRS
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Response of LOG_SP to IRS
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Response of LOG_ER to IRS
0 5 10 15 20 25 30 35 40 45 50
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0.000
-0.008 -0.004
0.008 0.004
-0.012 -0.016 -0.020
Note: Vertical axis - deviation from the baseline scenario, horizontal axis - number of months after the shock Source: own estimates based on JMulTi
Figure 5 plots the responses of financial variables in Romania to a monetary policy shock via the interest rate. Thus, our empirical results show that a positive monetary policy shock leads to a decrease in the industrial production index, the stock index and the loan to deposit ratio as in the case of previous countries. Also, in the short run the local currency appreciates, the pat- tern of response is similar to the Czech Republic. Unlike our results, Elbourne and de Haan (2006) find a positive relationship between industrial production and the interest rate using a SVAR model with data spanning the period 1998M06-2004M06, the authors’ explanation being the high level of inflation experienced by our country in that period. Albulescu (2010) using a regression model over the period January 2003-August 2008 finds that ROBID 3 months is not an efficient instrument of the central bank in order to correct imbalances related to evolution of asset prices. The difference from our results is due to the methodology used and period tested, as well. We can also say that we are witnessing a consolidation of the inter- est rate, as an instrument of monetary policy transmission in Romania, which is a fulcrum for an inflation targeting strategy (see, for example, Spulbăr et al., 2012).
Monetary policy and financial stability: empirical evidence from Central and Eastern European countries
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Figure 5 Responses of financial variables in Romania to an interest rate shock together with a 95% Hall bootstrap confidence interval based on 1 000 replications Response of LOG_IP to IRS
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Response of LOG_ER to IRS
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Figure 6 plots the responses of domestic variables in Bulgaria to a shock in the LIBOR EUR interest rate together with a 95% Hall bootstrap confidence interval based on 1000 replica- tions. We note that, in the short run, the industrial production index responds counter-intui- tively, but in the long run, the central forecast is negative and statistically significant. An ECB monetary policy shock via the interest rate drives down the loan to deposit ratio and share prices but the effects are only marginally significant.
Figure 6 Responses of financial variables in Bulgaria to a shock in the LIBOR EUR interest rate together with a 95% Hall bootstrap confidence interval based on 1 000 replications Response of LOG_IP to LIBOR
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Monetary policy and financial stability: empirical evidence from Central and Eastern European countries
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Response of LDR to LIBOR
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The impulse response analysis (figure 7) highlights a counter-intuitively and statistically sig- nificant response of the loan to deposit ratio for the banking system in Latvia after an ECB monetary policy shock. All the other variables react in line with economic textbooks.
Figure 7 Responses of financial variables in Latvia to a shock in the LIBOR EUR interest rate together with a 95% Hall bootstrap confidence interval based on 1 000 replications
Response of LOG_IP to LIBOR 0.6
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Figure 8 plots the responses of domestic variables in Lithuania to a shock in the LIBOR EUR interest rate together with a 95% Hall bootstrap confidence interval based on 1000 replica- tions. The responses of Lithuanian indicators are similar to those of Latvia. We also note a counter-intuitive response of the loan to deposit ratio which increases by 6% after roughly 15 periods. Unlike our results, Elbourne and de Haan (2006) find a negative relationship be- tween the interest rate and industrial production, but statistically insignificant.
Monetary policy and financial stability: empirical evidence from Central and Eastern European countries
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Figure 8 Responses of financial variables in Lithuania to a shock in the LIBOR EUR interest rate together with a 95% Hall bootstrap confidence interval based on 1 000 replications Response of LOG_IP to LIBOR
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Response of LOG_SP to LIBOR 0.04
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We observe that our empirical results differ according to monetary policy strategy in place and, therefore, we prefer to draw conclusions based on this criterion, as follows:
• countries operating under an inflation targeting regime (the Czech Republic, Hungary, Poland and Romania); • countries operating under a fixed exchange rate regime based on a currency board (Bul- garia, Lithuania) or fluctuation band (Latvia).
Table 1 Responses of financial variables to a monetary policy shock in the Czech Republic, Hungary, Poland and Romania (2003: M01 2012: M06)
Variables Country
CZ HU PO RO Expected
Industrial production index -* -* -* -* - Loan to deposit ratio -* -* -* -* - Stock prices -* -* -* -* - Exchange rate - - - -* -
Note: - negative response, * statistically significant response at 5% level Source: own estimates based on JMulTi
From the perspective of financial stability, our empirical results highlight the following:
• There is a statistically significant inverse relationship between the interest rate and stock prices in the Czech Republic, Hungary, Poland and Romania (table 1), which means that the interest rate represents an efficient instrument of intervention in order to correct evolu- tion of asset prices. • Since stock markets in the Czech Republic, Hungary, Poland and Romania are sensitive to unexpected changes in interest rates, a good alternative for investors would be to rely on interest rate forecasts to make investment decisions in the Czech, Hungarian, Polish and Romanian capital markets.
Monetary policy and financial stability: empirical evidence from Central and Eastern European countries
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• There is an inverse relationship between the interest rate and the loan to deposit ratio for the banking system in the Czech Republic, Poland and Romania (table 1). This means that the interest rate represents an efficient instrument of the central bank in order to pre- vent excessive borrowing by households and economic agents. A credit boom which is not accompanied by an increase in the level of deposits (which reflects confidence in the national currency) indicates a potential imbalance in the financial system and the fact that households and companies face the problem of informational asymmetry. • There is an inverse relationship between the exchange rate and the interest rate in all countries analyzed, irrespective of their exchange rate regime (free floating or managed floating). • The sensitivity of the exchange rate to interest rate evolution shows that the exchange rate regime is in compliance with use of inflation targets as a nominal anchor for monetary policy.
From the perspective of monetary policy, our empirical results highlight the following:
• Responses of macroeconomic variables to a monetary policy shock are similar in the Czech Republic, Hungary, Poland and Romania. The differences between countries con- sist in the number of periods (months) after the shock when these effects occur and in the persistence of the shocks. • The differences between countries analyzed concerning the magnitude and persistence of shocks show that it is not appropriate to formulate general monetary policy decisions. • All the macroeconomic variables move in the expected direction after a monetary policy shock. Therefore, we subscribe to Jarocinski (2010) who states that “we need to go be- yond the simple rule that monetary policy is less effective in less financially developed countries”. Economic and financial integration has reshaped the frameworks and trans- mission channels of monetary policy in emerging market economies (Mihaljek, 2011).
Empirical analysis shows that an inflation targeting strategy under a free or managed floating exchange rate is suitable for promoting financial stability.
Table 2 Responses of financial variables to ECB monetary policy shock in Bulgaria, Latvia and Lithuania (2003: M01 2012: M06)
Variables Country
BG LV LT Expected Industrial production index -* -* -* - Loan to deposit ratio -* +
* +
* - Stock prices -* -* -* -
Note: - negative response, + positive response, * statistically significant response at 5% level Source: own estimates based on JMulTi
The empirical results obtained for countries operating under a fixed exchange rate regime highlight the following:
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• In Bulgaria, after an ECB monetary policy shock all the variables react in line with eco- nomic theory. • A counterintuitive response of the loan to deposit ratio for the banking system in Latvia and Lithuania. Liquidity is not a constraint for banking systems whose loan/deposit ratio is under or near 100%. From this perspective, the Baltic countries are not in a comfortable position (see figure 2).
Figure 9. Evolution of the loan/deposit ratio in Latvia and Lithuania during 2006-2012 (%) 300
250
200
150
100
50
0 2006 2007 20092008
208.7
238.6 246.6 230.7 198 198 197.5
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Latvia Lithuania
Source: based on Eurostat data
Overall, the empirical results show that, in Latvia and Lithuania, countries which lost their monetary policy autonomy, adjustments in ECB monetary policy are not in accordance with country specific conditions. Moreover, our results provide some insights that when the in- terest rate is not controlled by the National Central Bank, households and economic agents face the problem of informational asymmetry. In this case, in the absence of a discretionary response from the central bank, preventive intervention would be more suitable, according to Albulescu (2010). We subscribe to measures proposed by this author, in order to monitor the development of asset prices, namely: strengthening supervision and regulation, respectively, reducing informational asymmetry. Among countries with a fixed exchange rate regime, only in Bulgaria is the transmission of the foreign interest rate impulse to the domestic variables conducive to financial stability. The impact of ECB monetary policy shock on Bulgarian macroeconomic variables is similar to countries which follow an inflation targeting strategy.
There are three main caveats of our analysis:
• The empirical results may be flawed by national differences in the definition of the loan portfolio for the banking system. • The residuals are not normally distributed in the case of Bulgaria, Hungary, Romania. • The small number of variables included in our stylized models. The impact of a mon- etary policy shock can be analyzed only for the variables included in the model, which are, generally, only a small fraction of the variables of interest for policymakers and re- searchers implicitly.
Our results are robust to different specifications. First, changing the order of variables does not affect the results. Secondly, the inclusion of dummy variables in order to account for
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changes in exchange rate regimes provides similar impulse response functions, but with larg- er confidence intervals.
5. Conclusions
Using a Structural Vector Autoregressive methodology and impulse response function, with data ranging from 2003M01 to 2012M06, we have analyzed the effectiveness of the short term interest rate in affecting selected asset prices.
Our empirical results differ according to monetary policy strategy in place. Therefore, the main findings regarding the safeguarding of financial stability in CEE countries operating under inflation targeting strategy (the Czech Republic, Poland, Hungary, Romania) are:
• The interest rate represents an efficient instrument of intervention in order to correct the evolution of asset prices and a good alternative for investors would be to rely on interest rate forecasts to make investment decisions in the Czech, Hungarian, Polish and Roma- nian capital markets. • The interest rate represents an efficient instrument of the central bank in order to prevent excessive borrowing by households and economic agents. • The sensitivity of the exchange rate to interest rate evolution shows that the exchange rate regime is in compliance with use of inflation targets as a nominal anchor for monetary policy.
On the other hand, the main findings regarding monetary policy in CEE inflation targeting countries are:
• Responses of macroeconomic variables are similar in the Czech Republic, Hungary, Poland and Romania. The differences between countries consist in the number of periods (months) after the shock when these effects occur and in the persistence of the shocks. • Differences between the countries analyzed concerning the magnitude and persistence of shocks show that it is not appropriate to formulate general monetary policy decisions.
Our empirical analysis shows that an inflation targeting strategy under a free or managed floating exchange rate is suitable for promoting financial stability.
Among countries with a fixed exchange rate regime, only in Bulgaria is transmission of the foreign interest rate impulse to domestic variables conducive to financial stability. The impact of ECB monetary policy shock on Bulgarian macroeconomic variables is similar to countries which follow an inflation targeting strategy. In the case of Latvia and Lithuania, adjustments in ECB monetary policy are not in accordance with country specific conditions, the loan to deposit ratio responds counter-intuitively to an unexpected increase in LIBOR.
Our contribution relative to the previous literature is twofold: an empirical exploration based on a structural VAR methodology applied to a number of CEE countries grouped by the degree of nominal exchange rate flexibility and a policy debate on the design of macro- prudential polices in the aftermath of the boom-bust cycle experienced by CEE countries in the second half of the last decade.
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The paper is useful to those involved in central bank activity, because it assesses the effective transmission of monetary policy impulses via the interest rate, as an instrument, on several macroeconomic variables, proxies for financial stability. Moreover, the paper contributes to the policy debate on the design of macro-prudential polices in the aftermath of the boom-bust cycle experienced by CEE countries in the second half of the last decade.
Further research is called for. Since the VAR models yield problems with respect to a limita- tion to the size of the system, a first development should be to apply a Factor Augmented VAR (FAVAR) in order to consider a very large data set for estimation as in Balabanova and Brüggemann (2012). A second development should be to conduct counterfactual scenarios using the estimated models in order to better demonstrate the effectiveness of the interest rate in dealing with financial instabilities.
Acknowledgements
This work was supported by the European Social Fund in Romania, under the responsibility of the Managing Authority for the Sectoral Operational Programme for Human Resources Development 2007-2013 [grant POSDRU/107/1.5/S/78342].
References
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MONETARY POLICY AND FINANCIAL STABILITY.pdf
MONETARY POLICY AS FINANCIAL STABILITY REGULATION∗
JEREMY C. STEIN
This article develops a model that speaks to the goals and methods of financial stability policies. There are three main points. First, from a normative perspective, the model defines the fundamental market failure to be addressed, namely, that unregulated private money creation can lead to an externality in which intermediaries issue too much short-term debt and leave the system excessively vulnerable to costly financial crises. Second, it shows how in a simple economy where commercial banks are the only lenders, conventional monetary policy tools such as open-market operations can be used to regulate this externality, whereas in more advanced economies it may be helpful to supplement monetary policy with other measures. Third, from a positive perspective, the model provides an account of how monetary policy can influence bank lending and real activity, even in a world where prices adjust frictionlessly and there are other transactions media besides bank-created money that are outside the control of the central bank. JEL Codes: E58, G01.
I. INTRODUCTION
The modern literature on monetary policy emphasizes the central bank’s role in fostering price stability.1 Historically, however, a dominant concern for central bankers has been not just price stability but also financial stability. Goodhart (1988) argues that the original motivation for creating central banks in many countries was to temper the financial crises associated with unregulated “free banking” regimes:
In the nineteenth century, the advocates of free banking argued that the banking system could be trusted to operate effectively without external con- straints or regulation. . . . [But] experience suggested that competitive pressures in a milieu of limited information (and, thence, contagion risks) would lead to procyclical fluctuations punctuated by banking
∗Eduardo Davila and Fan Zhang provided outstanding research assistance. I am grateful for comments from Robert Barro, Effi Benmelech, Ricardo Caballero, Emmanuel Farhi, Mark Gertler, Marvin Goodfriend, Robin Greenwood, Sam Hanson, Larry Katz, Arvind Krishnamurthy, Jamie McAndrews, David Scharfstein, Andrei Shleifer, Robert Vishny, the referees, and seminar partici- pants at numerous institutions. Thanks also to Mary Goodman, Sam Hanson, Matt Kabaker, Andrew Metrick, Charlie Nathanson, Larry Summers, and Adi Sunderam for a series of early conversations that helped shape the ideas in this article.
1. See, for example, Goodfriend (2007) for a recent articulation of this view.
c© The Author(s) 2012. Published by Oxford University Press, on the behalf of President and Fellows of Harvard College. All rights reserved. For Permissions, please email: journals. [email protected]. The Quarterly Journal of Economics (2012) 127, 57–95. doi:10.1093/qje/qjr054. Advance Access publication on January 6, 2012.
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panics. It was this experience that led to the forma- tion of noncompetitive, non-profit maximizing Central Banks. (p. 77)
A related emphasis on crisis mitigation is evident in Bagehot’s (1873) famous discussion of the lender-of-last-resort function.2 Certainly, recent events have served to underscore the importance of the central bank’s role in preserving financial stability.
In this article, I develop a model that speaks to the goals and methods of central bank financial stability policies. The first step is to define the fundamental market failure that needs to be addressed. I begin with an unregulated banking system in which banks raise financing from households to invest in projects. Banks can raise this financing in the form of either short-term or long-term debt. Households are risk-neutral with respect to fluctuations in their consumption, but derive additional monetary services from holding any claim that is entirely riskless—with the notion being that riskless claims are easy to value and hence facilitate exchange among households. I show that banks can manufacture some amount of riskless private “money” of this sort, thereby lowering their financing costs. Moreover, they can do so in greater quantity by issuing short-term debt, because it is harder for long-term bank debt to be made risk-free.
The role for financial stability policy arises because the pri- vate choices of unregulated banks with respect to money creation are not in general socially optimal. When banks issue cheaper short-term debt, they capture its social benefits, namely, the monetary services it generates for households. However, they do not always fully internalize its costs. In an adverse “financial crisis” state of the world, the only way for banks to honor their short-term debts is by selling assets at fire-sale prices. I show that in equilibrium, the potential for such fire sales may give rise to a negative externality. Thus, left to their own devices, unregulated banks may engage in excessive money creation and may leave the financial system overly vulnerable to costly crises.3
2. Tucker (2009) paraphrases Bagehot’s (1873) dictum as follows: “to avert panic, central banks should lend early and freely (i.e., without limit) to solvent firms, against good collateral, and at ‘high rates.”’
3. Gersbach (1998) and Hart and Zingales (2011) are other papers in which unregulated banks create a socially excessive quantity of private money. However, the externalities in these papers are unrelated to financial stability.
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There are a variety of ways for a regulator to address this externality. One possibility is the use of conventional monetary policy tools, that is, open-market operations. To see how monetary policy might be of value, note that a crude approach to dealing with the externality would be for the regulator to just impose a cap on each bank’s total money creation. However, when the regulator is imperfectly informed about banks’ investment opportunities, he will not know where to set the cap, since it is desirable for banks with stronger investment opportunities to do more money creation. In this setting, the regulator can do better with a flexible “cap-and-trade” system in which banks are granted tradable per- mits, each of which allows them to do some amount of money creation.4 The market price of the permits reveals information about banks’ investment opportunities to the regulator, who can then adjust the cap accordingly—when the price of the permits goes up, this suggests that banks in the aggregate have strong investment opportunities, so the regulator should loosen the cap by putting more permits into the system.
All of this may sound a bit like science fiction; we don’t observe cap-and-trade regulation of banks in the real world. However if banks’ short-term liabilities are subject to reserve requirements, it turns out that monetary policy can be used as a mechanism for implementing the cap-and-trade approach. When the central bank injects reserves into the system, it effectively increases the number of permits for private money creation. The nominal inter- est rate, which captures the cost of holding reserves, functions as the permit price. Thus, open-market operations that adjust aggregate reserves in response to changes in short-term nominal rates can be use to achieve the cap-and-trade solution.
An interesting benchmark case is where reserve require- ments apply to the money-like liabilities of all lenders in the economy. This allows the central bank to precisely control private money creation with monetary policy alone. Although this case may roughly capture the situation facing central banks at an earlier period in history, it is less realistic as a description of modern advanced economies. Nowadays there are a range of short-term financial intermediary liabilities that are not subject to reserve requirements, and yet may both provide monetary services and create fire-sale externalities. For example, Gorton
4. Kashyap and Stein (2004) suggest using an analogous cap-and-trade approach to implement time-varying bank capital requirements.
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and Metrick (2011), and Gorton (2010) argue that an important fraction of private money creation nowtakes place entirely outside of the formal banking sector, via the large volumes of short-term collateralized claims created in the “shadow banking” sector.
In this richer environment, monetary policy as convention- ally practiced is generally not sufficient to rein in excessive money creation. Continuing with the foregoing example, it may additionally be necessary to regulate the volume of activity in the shadow banking sector, either by expanding the reach of reserve requirements or by some other means. Thus the model helps make clear the circumstances under which monetary policy needs to be supplemented with other measures. Moreover, it sug- gests that these other measures lie squarely in the central bank’s traditional domain, to the extent that they are also targeted at the fundamental externality associated with excessive private money creation. This is of interest in light of the ongoing debate over the appropriate mix of central bank tools for achieving financial stability.5
In addition to its normative implications, the model is also relevant from a positive perspective. It provides a coherent account of how monetary policy “works”—that is, of how open market operations lead to changes in bank lending and output— in an environment that is arguably more realistic than in other theories. In contrast to the usual model, prices are fully flexible. Moreover, I do not need to assume that the central bank has monopoly control over all forms of transactions media. The model is unchanged if one introduces a set of nonreservable securities that provide the same monetary services as bank-created money.6
Indeed, I consider the limiting case where the interest rate spread between money and bonds is fixed and unresponsive to their rela- tive supplies. Monetary policy works in this case not by changing real interest rates but through a pure quantity effect: a loosening of policy allows banks to finance themselves with more of the cheaper money, which encourages them to do more lending.
5. See, for example, Adrian and Shin (2008) and Ashcraft, Garleanu, and Pedersen (2010).
6. To be clear on the distinction: my model assumes that the central bank acts as a regulator, controlling those forms of private money creation that lead to negative externalities—in particular, short-term bank debt that finances risky long-term assets. However, it does not require the central bank to control more benign forms of money creation, for example, money market fund accounts backed exclusively by Treasury bills.
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The ideas in this article connect to several strands of pre- vious work. First, the basic model of fire sales that creates the rationale for policy intervention draws on Shleifer and Vishny (1992, 1997).7 Second, the insight that banks create a valuable transactions medium by issuing low-risk claims is formalized in Gorton and Pennacchi (1990). Third, the notion that central bank reserves can be thought of as permits that allow banks to do more of a particular kind of cheap financing appears in Stein’s (1998) elaboration of the bank lending channel of monetary policy transmission.8
Finally, to focus on the financial stability consequences of monetary policy, it helps to set aside its effects on price stability. I do so by appealing to the fiscal theory of the price level, according to which the price level is determined not by the monetary base but by total outstanding nominal government liabilities—that is, by the sum of Treasury securities and the monetary base.9 This enables open market operations that change the mix of Treasuries and bank reserves (while keeping their sum constant) to have real effects on bank investment and financing behavior, even in a world where all prices are perfectly flexible. However, I also discuss how the model’s conclusions carry over to an alternative New Keynesian setting with sticky prices, where price stability is governed by a version of the “Taylor rule” (Taylor 1993, 1999).
The rest of the article is organized as follows. Section II devel- ops the basicmodel of private money creation by banks. Section III compares banks’ financing choices to the social planner’s solution and clarifies the conditions under which banks engage in excessive money creation. It also shows that a cap-and-trade approach to regulation can be useful when the social planner has imper- fect information. Section IV demonstrates how the cap-and-trade approach can be implemented with open market operations. Section V explores a number of other complementary policy tools; these include liquidity regulation, deposit insurance, and a lender-of-last-resort function, as well as regulation of the shadow
7. On fire sales, see also Kiyotaki and Moore (1997), Gromb and Vayanos (2002), Morris and Shin (2004), Allen and Gale (2005), Fostel and Geanakoplos (2008), Brunnermeier and Pedersen (2009), Stein (2009), Caballero and Simsek (2010), and Geanakoplos (2010).
8. For early work on the bank lending channel, see also Bernanke and Blinder (1998, 1992); Kashyap, Stein, and Wilcox (1993); and Kashyap and Stein (2000).
9. The fiscal theory is developed in Leeper (1991), Sims (1994), Woodford (1995), and Cochrane (1998). My own adaptation of the theory is particularly indebted to Cochrane’s exposition.
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banking sector. Section VI discusses how the model differs from other accounts of the monetary transmission mechanism. Conclu- sions are in section VII.
II. A MODEL OF PRIVATE MONEY CREATION
The model features three sets of actors: households, banks, and “patient investors.” I begin by describing each of these groups, and then turn to the optimization problem faced by the banks.
II.A. Households
There are three dates, 0, 1, and 2. At time 0, households have an initial endowment of the one good in the economy. They can either consume this endowment at time 0, or invest some of it in financial assets and consume the proceeds from investment at time 2. They have linear preferences over consumption at these two dates. In addition to consumption, households also derive utility from monetary services. The key assumption is that monetary services can be provided by any privately created claim on time 2 consumption, so long as that claim is completely riskless.10 Thus the utility of a representative household is given by:
(1) U = C0 + βE(C2) + γM,
where M represents the household’s time 0 holdings of privately created “money.”11 To be clear on the notational convention, when a household has M units of money at time 0, this means that it holds claims guaranteed to deliver M units of time 2 consumption.
10. This assumption is meant to capture the spirit of Gorton and Pennacchi (1990) and Dang, Gorton, and Holmstrom (2009). These papers argue that information-insensitive securities are an attractive medium of exchange because they eliminate the potential for adverse selection between transacting parties. My formulation implies that households do not derive monetary services from state- contingent deposits (as in Hellwig 1994). If they did, efficiency might be improved by having banks issue claims that pay a lower return in bad states of the world. However, if some agents have a better ability than others to forecast when the bad state is coming, such state-contingent claims would be subject to adverse selection problems.
11. In a similar formulation, Krishnamurthy and Vissing-Jorgensen (2010) put the stock of Treasury securities directly into the representative agent’s utility function. As one rationale for doing so, they cite the “surety” of Treasuries—that is, the fact that Treasuries are riskless. Like I do, they posit that surety has an extra value above and beyond what is captured in a standard asset pricing model. See also Sidrauski (1967) for an early model with money in the utility function.
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Given their linear form, household preferences pin down two real rates. The first is the (gross) real return on risky “bonds” that pay off at time 2, given by RB = 1
β . The second is the
(gross) real return on riskless “money,” given by RM = 1(β+γ) , where β + γ < 1. The latter follows from the observation that a household is always indifferent between having: (1) β + γ units of time 0 consumption; or (2) a riskless claim that promises one unit of time 2 consumption, since such a claim delivers β of utility from expected future consumption, along with an additional γ of utility in monetary services. The bottom line is that because riskless money offers households a convenience yield that risky bonds do not, in equilibrium it must have a lower rate of return.
The idea that money has a lower return in equilibrium than bonds is standard in textbook models. But here, the return spread is fixed and independent of the quantities of money and bonds, thanks to the linear preferences on the part of households. This feature is not necessary for anything that follows and is easily relaxed. However, it serves to highlight a key novelty of my model: here, changes in central bank policy work not by altering the real rates on either type of claim but by varying the proportions of each that banks use. In other words, looser policy encourages banks to lend more by enabling them to tilt their capital structure toward cheap money financing, thereby lowering their weighted average cost of funds.
II.B. Banks
Households cannot invest their time 0 endowments directly in physical projects, because they do not have the monitoring expertise to do so. This investment must be undertaken by banks, who in turn issue financial claims—in the form of either riskless money or risky bonds—to households. There is a continuum of such banks, with total mass of one. Each bank faces the following investment opportunities. If an amount I is invested at time 0, and the good state prevails, which happens with probability p, total output at time 2 is given by the concave function f (I) > I. If instead the bad state prevails, total expected output at time 2 is λI ≤ I, and there is a positive probability that output collapses all the way to zero. In particular, in the bad state, output is either λIq with probability q, or zero with probability (1 − q).
At time 1, there is a public signal that reveals whether the good or bad state will be realized at time 2. At time 1 it is also
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possible for a bank to sell any fraction of its existing physical assets to a patient investor.12 If a fraction Δ of the assets are sold, total proceeds to the bank are given by Δ kλI, where 0 ≤ k ≤ 1, and the remaining unsold assets yield output at time 2 to the bank of (1−Δ)λI. Thus k is a measure of the discount to expected value associated with a time 1 asset sale. A central feature of the model is that k is endogenous and depends on total asset sales by all banks in the economy. The equilibrium determination of k will be discussed shortly.
Other than their access to investment opportunities, banks have no initial endowments, and hence must raise the entire amount I externally. They can do so by issuing either short-term (maturing at time 1) or long-term (maturing at time 2) debt claims to households. Note that if they finance with long-term debt, no amount of this debt can ever be riskless, because there is a positive probability of the assets yielding zero output at time 2. By contrast, short-term debt can be made riskless, if not too much is issued. This is because by forcing an asset sale on seeing a bad signal at time 1, short-term creditors can escape early with a sure value equal to the proceeds from the sale.
These assumptions are starker than they need to be. In a more general model where the lowest possible value of output at time 2 is greater than zero, banks can issue some riskless long- term debt—so there is no longer a one-to-one mapping between debt maturity and the ability for debt to be made risk-free. Nevertheless, it will always be the case that banks can create a larger quantity of riskless claims by issuing short-maturity debt; the early escape intuition still holds. Because there is a fixed premium on riskless claims, banks will continue to be tempted to issue short-term debt in this more general version of the model, and all the qualitative results that follow will continue to apply.
The model can also be extended so that monetary services are provided not only by entirely riskless assets but by any claims that are sufficiently low risk—that is, by any claims whose worst-case payoff is at least x cents on the dollar. What is critical is that there still be a violation of the Modigliani and Miller (1958) conditions, so that as a bank manufactures more of these low-risk money-like claims, it does not have to pay more for its remaining long-term debt, which becomes riskier. This M-M violation is captured here
12. Because households only consume at time 0 and time 2, they do not consume the proceeds of any time 1 asset sales until time 2. One can think of them as simply sitting on these proceeds in the interim.
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in the assumption that the return on nonmonetary claims, RB, is a constant.
In any of these formulations, the key trade-off is this: on one hand, banks have an incentive to issue some short-term debt, because more of this debt can be made low-risk—and hence by virtue of its money-ness, represents a cheap form of finance.13
On the other hand, what keeps short-term debt safe is the bank’s ability to sell assets in the bad state. As will become clear, these sales of existing assets can lead to social costs that are not always fully internalized by individual banks when they pick their capital structures. As a result, there may be excessive private money creation by banks.
Suppose that a bank raises a fraction m of its total investment of I by issuing short-term debt. If this short-term debt can be made riskless, it will carry a rate of return of RM , and the bank will owe its short-term creditors a repayment of mIRM ≡ M. Can it meet this promise in the bad state by selling assets if necessary? From before, if it sells a fraction Δ of its assets, total proceeds are Δ kλI, so we require that:
(2) Δ kλI = mIRM , orΔ = mRM
kλ .
Since Δ ≤ 1, there is an upper bound on private money creation given by:
(3) mmax = kλ RM
.
Thus, the potential for asset sales makes it possible for a bank to create riskless private money by issuing short-term debt—as long as the amount issued is not too large.
Is it also the case that asset sales are an unavoidable con- sequence of money creation? One might think that since holding on to assets is positive NPV relative to selling them at time 1, it might be possible for a bank to raise new funding at time 1 to pay off the departing short-term creditors, and thereby avoid forced sales. However, if one assumes that any new funding must be subordinated to existing long-term debt, such new funding may be blockaded by a severe debt overhang problem (Myers 1977),
13. Other theories of short-term financing include Flannery (1986), Diamond (1991), and Stein (2005), who stress its signaling properties, and Diamond and Rajan (2001), who argue that short-term debt is a valuable disciplining device, particularly for financial intermediaries.
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given the low value of the assets in the bad state relative to the total face amount of already-issued debt.14 Thus, under plau- sible circumstances, private money creation inevitably leads to some amount of asset sales.15
Note that I assume that banks invest all the resources that they raise at time 0 in real projects and do not hold any back as a buffer against a loss of funding at time 1. However, this is without loss of generality, since a bank always has the option to change the mix of its short-term versus long-term debt, which has a similar buffering benefit and is more cost-effective. In other words, there are two ways to reduce asset sales in the bad state by $1: either borrow an extra dollar of long-term debt at time 0 and park the proceeds in storage, or borrow an extra dollar of long-term debt at time 0 so as to reduce the amount of short-term borrowing by $1. The net cost of the former transaction is (RB − 1), and the net cost of the latter is (RB − RM ). Hence, the latter approach is strictly preferred, and banks endogenously choose not to engage in storage.
Before moving on, it is worth fleshing out an issue of inter- pretation about the banks in the model. In the real world, banks do not invest in physical projects directly, but lend to firms who in turn do the project selection. Abstracting away from this extra layer of activity, as I do here, is tantamount to assuming that there are no contracting frictions between operating firms and banks, that is, that firms can costlessly pledge all of their output to the banks. This raises the question of whether it is appropri- ate to interpret what I label “banks” as really being financial
14. In particular, denoting the face value of the existing long-term debt by B, it must be that M + B > I, for the bank to have raised I at time 0 by issuing money and bonds. If the bank now wants to raise an amount M to pay off the short-term creditors in the bad state at time 1, it must do so by issuing new claims that are junior to the existing long-term debt. But given that they are junior, the value of these claims in the bad state is only q(λI/q − B). For q large enough (certainly for q > λ) the value of the new claims is necessarily less than M, so refinancing the short-term debt is impossible.
15. This line of argument leaves open the question of why the original long- term financing for the bank is in the form of senior debt, as opposed to, say, equity, or some other junior security that allows for new financing to come in on top of it. Following Hart and Moore (1995), it may be that this seniority of the long- term debt represents a valuable precommitment in the more likely good state of the world. For example, it may prevent managers from using assets in place as collateral for empire-building investments. Thus, as in Hart and Moore, senior long-term debt is a double-edged sword: it serves to discipline wayward managers in the good state, but forces underinvestment (here, in the form of asset sales) in the bad state.
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intermediaries, as opposed to operating firms that borrow directly from households in the securities market.
To create a meaningful distinction, suppose that any individ- ual operating firm, once funded, always has some probability of immediate (i.e., before time 1) idiosyncratic failure, in which case it becomes publicknowledge that its output will be zeroin both the good and bad states. This risk of failure makes it impossible for an operating firm to ever issue riskless claims in any amount. Banks, on the other hand, represent highly diversified portfolios of such firm-level projects, and therefore their assets always have positive expected value as of time 1, as assumed. The diversification associated with banks is thus a necessary condition for them to create riskless claims.16
II.C. Patient Investors
Patient investors (PIs) are another type of intermediary, and as such, any output that they produce reverts to the household sector at time 2. As a group, PIs are endowed with resources of W at time 1. For simplicity, I treat this endowment as exogenous for now, but it can be endogenized by allowing the PIs to raise the W from the household sector at time 0 by issuing risky long-term claims. In this case, the PIs choose an optimal level of W at time 0 that equates the expected return on their time 1 investments to the cost of capital RB. Imposing this ex ante breakeven condition does not affect the qualitative results of the model, so I set it aside for the time being.
What is crucial is that when time 1 rolls around and the state of the world is realized, W is fixed. Thus, although it is fine to think of PIs as having full access to financial markets at time 0, they cannot go back and raise more at time 1 once they know the state. In other words, W is an unconditional war chest, with the same amount available to PIs in the good and bad states. This assumption can be thought of as a crude stand- in for the phenomenon of “slow-moving capital” (Duffie 2010). A more explicit micro-foundation might involve an information asymmetry between PIs and households at time 1—for example, the PIs get a private signal about the quality of their investment
16. Thus, as in other models of intermediation, both pooling (i.e., diversifica- tion) and tranching (i.e., the issuance of properly structured senior securities) have roles to play in creating low-risk claims. See, for example, Gorton and Pennacchi (1990), DeMarzo and Duffie (1999), and DeMarzo (2005). Diamond (1984) also emphasizes the importance of diversification to the process of intermediation.
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opportunities at this time, which creates an adverse selection problem for any further attempts to raise financing.
PIs can do one of two things with their resources at time 1. First, they can invest in new, late-arriving real investment projects. Irrespective of the state of the world, an investment of K in such new projects at time 1 yields expected gross output of g(K) at time 2, where g( ) is a concave function. Alternatively, PIs can absorb assets being sold by banks at time 1. In the good state, there are no asset sales, so the PIs invest all of W in new projects, yielding g(W). In the bad state, banks have to sell enough assets to repay short-term creditors the M they have promised them. Thus in equilibrium, PIs spend M on asset purchases, and invest only (W − M) in new projects, yielding g(W − M). For the PIs to be willing to allocate their endowment in this way, it must be that the marginal return on new projects is the same as the marginal return from buying existing assets from banks. This is what pins down the fire-sale discount k. In particular, we have that:
(4) 1 k
= g′(W − M).
Equation (4) makes clear the real costs of fire sales, and hence of short-term debt financing by banks. The greater is M, and hence the more bank assets that the PIs have to absorb in the bad state at time 1, the less they have left over for investment in new projects. With scarce PI capital, the return on secondary market arbitrage opportunities (buying up fire-sold assets) also becomes the hurdle rate for new investment, a point emphasized by Diamond and Rajan (2009) and Shleifer and Vishny (2010).
For expositional purposes, I treat the PIs and the banks as two distinct categories of intermediaries. This is not necessary; one could alternatively merge them into a single entity that has investment opportunities at both time 0 and time 1, issues some short-term debt at time 0, and also holds liquidity W in reserve at time 0. This reinterpretation of the model is innocuous, subject to one caveat: it is crucial that the merged entities behave not as autarkic islands but as price-takers who can transact in the asset market at time 1. Thus, even if a bank satisfies most of its departing creditors by drawing down on its own stock of liquidity at time 1, it must continue to consider the possibility of asset sales to another bank. This feature emerges naturally if we move away from the knife-edge case where the scales of time 0 and time 1 investment are in identical proportions across all banks.
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If so, those that have relatively bigger time 1 scale will tend to stockpile more W relative to their short-term debts, and hence will be buyers of assets from those who have bigger time 0 scale. My two-categories formulation can be thought of as capturing an extreme case of this heterogeneity.
II.D. The Bank’s Optimization Problem
I formulate the optimization problem for a bank that invests an amount I and finances it with some fraction m ≤ mmax of money. The bank’s expected net profits at time 2 are given by:
(5) Π = {pf (I) + (1 − p)λI − IRB} + mI(RB − RM )− (1 − p)zmIRM ,
where I have defined z = (1−k)k as the net rate of return on fire-sold assets. (Note that higher values of z correspond to larger fire-sale discounts, and z = 0 is the case where there is no discount.) The three terms in equation (5) are easily interpreted. The first, {pf (I) + (1 − p)λI − IRB}, is the NPV of investment assuming that it is entirely financed at the higher bond market rate—and hence that there is no need to ever sell assets. The second term, mI(RB−RM ), is the financing cost savings associated with using a fraction m of money in the capital structure. The last term, (1 − p)zmIRM , captures the expected fire-sale losses associated with this riskier short-term capital structure.
Each bank picks m and I to maximize equation (5), subject to the collateral constraint that m ≤ mmax = kλ
RM . I assume that each
bank treats the fire-sale discount k as a fixed constant—that is, they do not internalizxe the incremental impact of their choices on the fire-sale outcome. By contrast, when I examine the social planner’s problem, the key difference will be that the planner takes into account the dependence of k on the capital structure of the banks. The Lagrangian for the bank’s problem is thus: (6)
LB ={pf (I) + (1−p)λI−IRB} + mI(RB−RM )−(1−p)zmIRM−η(m− kλ RM
),
where η is the shadow value of the collateral constraint. Taking the first-order condition with respect to m, we have:
(7) I{(RB − RM )− (1 − p)zRM} = η.
It follows that the collateral constraint binds, and the bank is at a corner, setting m = mmax, if (RB −RM ) > (1−p)zRM , that is, if the equilibrium spread between bonds and money is sufficiently
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large. Alternatively, if the spread is smaller in equilibrium (that is, if (RB − RM ) = (1 − p)zRM ), then the bank chooses an interior value of m, and η = 0.
The first-order condition with respect to I yields:
(8) pf ′(I) + (1 − p)λ− RB + m(RB − RM )− (1 − p)zmRM = 0.
Using equation (7), we can rewrite equation (8) as follows:
(9) pf ′(I) + (1 − p)λ− RB = −ηm
I .
There are two ways that equation (9) can be satisfied. First, the bank can be at an interior solution with respect to m, in which case η = 0, and therefore pf ′(I) + (1 − p)λ = RB. Alternatively, the bank can be at a corner with m = mmax, and η > 0, in which case it follows that pf ′(I) + (1 − p)λ < RB. This reasoning leads to the following proposition.
PROPOSITION 1. Define IB as the optimal level of investment for a bank that finances itself exclusively in the long-term bond market: pf ′(IB) + (1 − p)λ− RB = 0. The solution to the bank’s problem involves two regions. In the low-spread region (for (RB − RM ) relatively small) the bank chooses m < mmax and I∗ = IB. In the high-spread region (for (RB − RM ) relatively large) the bank chooses m = mmax and I∗ > IB.
The point to take away from the proposition is that in the low-spread region, a bank’s investment and financing choices are decoupled, whereas in the high-spread region they are interde- pendent. This is because when m < mmax, a bank’s ability to tap low-cost money financing is not constrained by the amount of investment it does. By contrast, in the high-spread region in which m = mmax, a bank faces a binding collateral constraint—it can only issue more money if it increases the quantity of physical assets backing its debts. This is what ties investment and financing decisions together. If money financing is cheap enough that banks want to do a lot of it, and they begin to bump up against the collateral constraint, they will be induced to invest more so as to loosen the constraint.
III. SOCIALLY EXCESSIVE MONEY CREATION: A ROLE FOR REGULATION
The next step in the analysis is to identify the circumstances in which the process of private money creation already described
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involves an externality—that is, when the level of money creation chosen by banks exceeds that preferred by a benevolent social planner.
III.A. The Social Planner’s Problem
Given that all output of the banks and the PIs ultimately accrues to the household sector, the social planner seeks to maximize the utility of a representative household, as given by equation (1). It is easily shown that, disregarding constants, this utility, expressed in units of time 2 consumption, is equivalent to:17
U = {pf (I) + (1 − p)λI − IRB} + M (RB − RM)
RM + pg(W)(10)
+(1 − p){g(W − M) + M}− WRB.
Comparing this to the bank’s expected profits in equation (5), we can see that the first two terms coincide. The difference is in the latter three terms: the planner does not care about expected fire-sale losses per se, because these only represent a transfer from the banks to the PIs. However, the planner does care about the net expected returns to investment by the PIs, as captured by pg(W)+ (1 − p){g(W − M) + M}− WRB.
The planner faces the same collateral constraint as the banks, namely, that m ≤ mmax = kλ
RM . Denoting the shadow value of the
constraint in this case by ηP, and recalling that M = mIRM , the Lagrangian for the planner’s problem is given by:
LP = {pf (I) + (1 − p)λI − IRB} + mI (
RB − RM )
+ pg(W)(11)
+ (1 − p){g(W − mIRM ) + mIRM}− WRB −ηP (
m − kλ RM
) .
In taking the first-order conditions for this problem, it is important to note that unlike an individual bank, the planner recognizes the dependence of k on the average behavior of all banks—he understands that, as per equation (4), k = 1
g′(W−mIRM ) .
17. In particular, suppose households have a fixed time 0 endowment of Y, and that they invest I of this endowment with the banks and W with the PIs at time 0. It follows that C0 = Y − I − W, and that C2 = f (I) + g(W) with probability p, and C2 = λ I + g(W − M) + M with probability (1 − p). The expression in equation (10) then follows from also including the monetary services γM in the utility function, and multiplying time 0 values by RB to put everything in common units of time 2 consumption.
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Using this fact, the first-order condition with respect to m can be written as:
(12) I{(RB − RM)− (1 − p)zRM} = ηP (
1 − g′′( ∙ )
(g′( ∙ ))2 λI
)
.
Similarly, the first-order condition with respect to I can be expressed as: (13)
pf ′(I)+ (1−p)λ−RB + m(RB−RM )−(1−p)zmRM =−ηP g′′( ∙ )
(g′( ∙ ))2 λm.
Comparing equations (7) and (12), and equations (8) and (13), we can see that the bank’s private solution coincides exactly with the social planner’s solution in the low-spread region where (RB − RM ) = (1 − p)zRM , and where the collateral constraint is nonbinding, that is, where η = ηP = 0. In this case, equation (13) reduces to equation (8), meaning that the planner chooses the same level of I as the bank.
By contrast, in the high-spread region where the constraint binds, so that ηP > 0, the term on the right-hand side of equation (13), −ηP g
′′(∙) (g′(∙))2 λm, describes the wedge between the bank’s solu-
tion and the planner’s solution. Since g′′( ∙ ) < 0, this term is positive, which implies that the marginal product of investment is higher in the social planner’s solution, or alternatively that I is lower. In other words, in this region, the social planner would like to restrain investment, and hence money creation, relative to the private outcome.
The following proposition summarizes the analysis.
PROPOSITION 2. Denote the private and socially optimal values of investment I by I∗ and I∗∗, respectively, and similarly for the private and socially optimal values of money creation M. In the low-spread region, I∗ = I∗∗, and M∗ = M∗∗. In the high- spread region, I∗ > I∗∗, and M∗ > M∗∗.
Thus banks may create a socially excessive amount of money, but this happens only if the spread between money and bonds (RB−RM ) is high enough. If the spread is solowthat any individual bank choose an interior value of money creation m < mmax, there is no divergence between private and social incentives.
EXAMPLE 1. Pick these functional forms and parameter values: f (I) = ψlog(I) + I, g(K) = θlog(K), RB = 1.04; RM = 1.01; ψ = 3.5; θ=150; λ=1; W =140; and p=0.98. For these values, the private
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FIGURE I
Private and Socially Optimal Outcomes versus the Money-Bond Spread
The figure plots private and socially optimal values of money creation M and investment I as a function of RM . Functional forms and parameter values are as follows: f (I) = ψlog(I) + I; g(K) = θlog(K); RB = 1.04; ψ = 3.5; θ = 150; λ = 1; W = 140; and p = 0.98. RM varies between 1.0 and 1.035.
optimum is in the high-spread region and involves banks choosing M∗ = 57.6 and I∗ = 104.9, with an associated rate of return on fire-sale assets of z = 82.1% (k = 0.549). By contrast, in the social optimum, the planner chooses M∗∗ = 55.2 and I∗∗ = 97.7, leading to a rate of return on fire-sale assets of z = 77.0% (k = 0.565).
Figure I expands on Example 1, keeping all of the other parameter values the same as before, but allowing RM to vary between 1.00 and 1.035, thereby causing the bond money spread (RB − RM ) to vary between 50 and 400 basis points. As can be seen, for low values of the spread, the private and socially optimal values of M and I coincide. But as the spread widens, these values diverge further and further from one another.
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III.B. Understanding the Nature of the Externality
At first glance, it may not be clear why fire sales create a divergence between private and socially optimal outcomes. After all, the price impact of liquidations is a pecuniary externality, and pecuniary externalities by themselves need not lead to violations of the standard welfare theorems. The result in Proposition 2 is a specific case of the generic inefficiency result in economies with incomplete markets (Geanakoplos and Polemarchakis 1986; Greenwald and Stiglitz 1986). Perhaps the closest analogs are Caballero and Krishnamurthy (2003) and Lorenzoni (2008), who also show how there can be socially excessive borrowing in economies with various financial frictions. In the current setting, the key friction is the presence of a binding collateral constraint. When this constraint is operative, any one agent’s impact on mar- ket prices affects other agents not only by altering their budget constraints but also by loosening or tightening their collateral constraints. The first welfare theorem effectively says that pecu- niary externalities that operate solely through prices in budget constraints do not lead to inefficiencies, but when prices show up elsewhere, this conclusion no longer holds.
The importance of the collateral constraint can be seen in the expression for the wedge between the bank’s first-order con- dition and that of the planner; as noted, this wedge is given by: −ηP g
′′(∙) (g′(∙))2 λm. Thus when the collateral constraint does not bind,
that is,when ηP = 0, there is no wedge, and the private and social solutions coincide. By contrast, when the collateral constraint binds, there is a wedge to the extent that g
′′(∙) (g′(∙))2 < 0, that is, to
the extent that an increase in liquidations widens the fire-sale discount, or equivalently, raises the marginal product of time 1 investment by the PIs.
The intuition behind this result can be understood as follows. When the constraint does not bind, equation (7) tells us that in deciding howmuch money tocreate, each bank trades offthe lower financing cost (RB−RM ) associated with money against the poten- tial for greater fire-sales discounts (1 − p)zRM . But according to equation (12), this is exactly the same trade-off the planner faces in attempting to balance the marginal value of monetary services to households against the marginal cost of underinvestment by the PIs. Hence in this case, everything is well internalized.
By contrast, when the constraint binds, and each bank is setting m = mmax, an incremental increase in money creation by
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MONETARY POLICY AS FINANCIAL STABILITY 75
any one bank has an added effect: by reducing the equilibrium value of k, it effectively lowers the collateral value of all other banks’ assets, thereby tightening their collateral constraints and impinging on their ability to create money. Thus, when any one bank creates an additional unit of money and captures the private benefit for doing so, the social benefit is less than that one unit of money, because other banks can no longer produce as much M for a given level of I.18
The result that there is no externality in the low-spread region when m < mmax is dependent on the strong assumption that when the PIs invest in real projects, they capture all the social surplus associated with these projects. If one adds another finan- cial friction to the model, and makes this surplus only partially pledgeable, private money creation is always socially excessive, irrespective of parameter values. In particular, suppose that the social return toan investment project financed by a PI is still given by g(K), but onlyϕg(K) can be pledged tothe PI, with ϕ < 1. In this case, the equilibrium determination of k in (4) is altered so that 1 k =ϕg
′(W−M). That is, a given amount of underinvestment by the PIs is now associated with a smaller fire-sale discount. Hence, a bank’s aversion to fire sales no longer leads it to fully internalize the social costs of underinvestment.
This imperfect pledgeability variant of the model is briefly explored in the Appendix. Because it is possible to make many of the key normative points that follow without introducing imperfect pledgeability, there is a certain minimalist appeal to focusing on the perfect pledgeability limit of ϕ = 1, as I do in the remainder of the text. However, if one is interested in generating more realistic comparative statics along some dimensions, the augmented version of the model that allows for ϕ < 1 may be better suited to doing so. For example, I show in the Appendix that the perfect pledgeability version of the model yields the some- what counterintuitive implication that the central bank should lower nominal interest rates when the risk of a financial crisis is greater. If instead we posit that ϕ < 1, this result can easily be reversed.
18. Think of two banks, A and B, as factories that each have a technology for producing money out of physical assets. When the collateral constraint binds, an incremental increase in money production by A is equivalent to a form of pollution that gums up B’s production technology, since it reduces the amount of money that B can manufacture out of a given stock of physical assets.
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III.C. A “Cap-and-Trade” Approach to Bank Liquidity Regulation
The analysis thus far makes clear that in some cases banks will choose to create more money than is socially optimal, thereby inflicting inefficiently high levels of fire sales on the economy. This suggests a role for regulation. In the full information case, in which the regulator observes all the relevant parameters of the model, the social optimum can be easily implemented with a cap on money creation: each bank can simply be prohibited from issu- ing more short-term claims than the desired level of M∗∗, which the regulator can directly compute from equations (12) and (13).
However, if the regulator is imperfectly informed, it becomes more challenging to set the cap appropriately.19 Consider a situ- ation in which banks know the productivity of their investment opportunities—that is, they know what the function f (I) looks like—but the regulator does not. As can be seen from equation (13), the value of I∗∗, and hence the value of M∗∗, depends on the marginal product of investment f ′(I). Intuitively, it makes sense to allow banks to create more cheap money financing when they have better investment opportunities. Thus without knowledge of the value of f ′(I), it is impossible for the regulator to target the socially optimal level of money creation with a simple cap.
One way for the regulator to generate the required informa- tion is through a system of cap and trade. In particular, each bank can be granted permits that allow it to issue some amount of money; by picking the aggregate quantity of permits, the regulator can, as before, effectively target the total amount of money M in the economy. Moreover, if the permits can be traded among banks, their market-clearing price P(M) (per unit of money creation allowed) will equal the shadow value of the M-constraint to the banks:
P(M) = dΠdM = 1
mRM dΠ dI .
20 Conditional on the regulator knowing the other parameters of the model, observing dΠdI allows him to infer the value of f ′(I).
It follows from this reasoning that the regulator can imple- ment the M∗∗ solution by making the permits tradable, and then
19. Weitzman (1974) is the seminal paper on regulation in the face of param- eter uncertainty.
20. Note that because the banks in the model are all identical, the volume of trade in the permits is zero. Nevertheless, there is a unique equilibrium price, given by the common shadow value of the M-constraint.
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targeting the appropriate price for these permits by varying the available quantity. That is, the regulator adjusts the quantity of permits, looking for a fixed point where the market-clearing price P(M) equals a target value PT (M) that itself depends on the quantity of permits. To calculate this target value, recall that in the high-spread region when m = mmax, the social optimum involves dΠdI = −η
P g ′′(∙)
(g′(∙))2 λm, which would imply setting P T (M) =
1 mRM
dΠ dI =
−ηPλ RM
. g ′′(∙)
(g′(∙))2 . Using equation (12), we can substitute for
ηP to obtain the following result.
PROPOSITION 3. A regulator who is imperfectly informed about the nature of bank lending opportunities can implement the desired level of money M∗∗ with a system of tradable permits for money creation. This involves adjusting the number of permits such that their observed market-clearing price P(M) equals the following target price PT (M):
(14) PT (M) =
{ (RB − RM )
RM − (1 − p)z
}
−λI g ′′(∙)
(g′(∙))2( 1 −λI g
′′(∙) (g′(∙))2
)
.
To be clear on the implementation, suppose the regulator picks an initial trial value of M. At this value, the regulator can calculate the target price of permits PT (M) from equation (14), based on his knowledge of M and the other observable parameters of the model—as can be seen from equation (14), he does not need to know anything about the value of f ′(I) to evaluate PT (M). If the market price of permits P(M) turns out to be higher than PT (M), the regulator increases M, and vice versa. The optimum M∗∗ is that value of M where the target price in equation (14) coincides with the market price.
EXAMPLE 2. Keep everything the same as in Example 1: f (I) = ψlog(I) + I, g(K) = θlog(K), RB = 1.04; RM = 1.01; ψ = 3.5; θ = 150; λ = 1; W = 140; and p = 0.98. At the social optimum of M∗∗ = 55.2, the price of permits is P = 0.0056. Now suppose there is a positive productivity shock, and ψ rises to 4.0. If the cap is not adjusted, the price of permits spikes to P = 0.0146. However, this price increase reveals the new value of ψ to the regulator, who can increase the number of permits in the system, raising the quantity of money in the system to its new optimal value of M∗∗ = 58.9. At this new optimum, the price of permits is given by P = 0.0054.
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The example suggests that in the face of productivity shocks, it is optimal for the regulator to actively lean against incipient changes in the price of permits. When a positive shock pushes the price of permits up, the regulator should increase the supply of permits, thereby driving their price back down. In fact, optimality in this setting requires the supply response to be sufficiently strong that the equilibrium price of permits actually falls slightly as productivity rises.
III.D. Relationship to Pigouvian Taxation
A handful of recent papers have suggested that a system of Pigouvian taxes might be used to force banks to properly internalize any systemic externalities they create (e.g., Jeanne and Korinek 2010; Kocherlakota 2010; Perotti and Suarez 2010). In the current context, this would amount to imposing a tax τ on each unit of money created by banks. A couple of points about such taxes are worth noting.
First, in the full information case where the planner observes everything needed to compute the socially optimal level of money creation M∗∗, this outcome can be achieved equally well either with a regulatory cap on money creation, or by picking the correct value of the taxτ. Indeed, given full information, the regulator can implement M∗∗ simply by setting τ = PT (M∗∗), that is, the target price of permits given by equation (14), calculated at the desired value of M∗∗. So Pigouvian taxes can be used, but in this setting they do not add any value relative to more conventional quantity- based regulation.
Second, in the incomplete information case where the planner does not knowenough topick the right level of the cap, he alsodoes not know enough to set the correct value of the tax τ, because the optimal tax depends on M∗∗. Thus, an optimal system of Pigouvian taxation still requires a mechanism to elicit the private information. So the cap-and-trade design remains useful, for the same reasons as before. Indeed, one can interpret the cap-and- trade approach as a “smart” system of Pigouvian taxation, since for any individual bank the permit price is identical to the optimal tax on money creation.21
21. This is not to say that cap-and-trade is the unique way of implementing the optimal scheme. An alternative would be an iterative form of taxation: the regulator announces a trial value of the tax rate. He then observes the quantity of M chosen by banks and uses this to infer the productivity of their investment opportunities. With these data, he can then set the optimal tax rate. Thus rather
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IV. IMPLEMENTING THE CAP-AND-TRADE APPROACH WITH MONETARY POLICY
The cap-and-trade approach to bank regulation may seem alien—it does not have any direct counterpart in the real world. However, I argue that the cap-and-trade approach can be imple- mented with something that looks very much like conventional monetary policy—with open market operations in which the cen- tral bank adjusts the quantity of nominal reserves in the banking system. In this setting, reserves play the role of permits for money creation, given the existence of a binding reserve requirement. And the nominal interest rate corresponds to the price of the permits.
In drawing this analogy, one wrinkle is that I have so far been working in an entirely real economy. To introduce a central bank and a role for monetary policy, I need to bring in a set of nominally denominated government liabilities, and then pin down the price level. To do so, I rely on the fiscal theory of the price level (Leeper 1991; Sims 1994; Woodford 1995; Cochrane 1998). In particular, the government is assumed to issue two types of nominal liabilities: Treasury bills and bank reserves. According to the fiscal theory, the sum of these two nominal liabilities is what is relevant for determining the price level. Given the sum, the composition of these liabilities is a real variable, since only reserves can be used tosatisfy reserve requirements. Thus holding fixed total government liabilities, when there are more reserves, banks are able to create more money, that is, to finance a greater fraction of their operations with short-term debt. Hence, reserves correspond exactly to the concept of regulatory permits in the real model.22 By contrast, if Treasury bills could also be used to satisfy reserve requirements, there would be nothing special about reserves, and open market operations would have no effect.
To operationalize the fiscal theory, I assume that the govern- ment anticipates real tax revenues of T at time 2, and the value of T is exogenously fixed. At time 0, the government has total nominal liabilities outstanding of l0, composed of Treasury bills b0, and bank reserves r0. Thus l0 = b0 + r0. The time 0 price level Λ0, is then determined by the requirement that the real value of
than setting quantities and learning from market prices, the regulator sets prices (taxes) and learns from market-determined quantities.
22. Since the price level is pinned down by fiscal considerations, the goal of achieving price stability cannot be the central bank’s job. Rather, the central bank is left with just the role of financial stability regulator.
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the government’s obligations must equal the present value of its future tax revenues:
(15) l0 Λ0
= T
RM .
Two points are worth noting here. First, the relevant real discount rate for the government is RM , given that its obligations are riskless: when households own Treasury bills, they derive the same monetary services from these bills that they do from privately created bank money, so the return on Treasury bills is equal to RM . Second, to keep real tax revenues fixed at T as the composition of government liabilities varies, I assume that the government rebates any seignorage revenues derived from the issuance of non–interest-bearing reserves in a lump-sum fashion to the household sector.23
Again, the key distinction between Treasury bills and bank reserves is that only the latter can be used to satisfy reserve requirements. In particular, any bank wishing to issue a dollar of short-term debt must hold ρ dollars of reserves, where ρ is the fractional reserve requirement. Hence the net amount of short- term debt financing made possible by $1 of reserves is (1−ρ)
ρ
dollars.24 It follows that in real terms, the total amount of M that can be created by the banking sector is now given by:
(16) M = (1 −ρ)r0 ρΛ0
= (1 −ρ)T ρRM
r0 l0
.
This expression makes it clear that the ratio of r0 to l0— namely, the composition of the government’s nominal liabilities— is a real variable, and is the means by which the government can target total real money creation by banks. An open market operation that increases the supply of reserves relative to T-bills is isomorphic to an increase in the regulatory limit on M in the all-real cap-and-trade version of the model.
23. Without this assumption, the composition of government liabilities would influence real tax revenues. In particular, as the government issued more non– interest-bearing reserves and fewer interest-bearing bills, its effective tax rev- enues would go up through a seignorage mechanism. The assumption can be loosely motivated by the idea that the government has some kind of social compact with its citizens that prevent it from letting total tax revenues—no matter how they are raised—go above T.
24. As an example, suppose ρ = 0.10. In this case, with $1 of reserves, a bank is allowed to raise $10 of short-term debt. But given that it must hold the reserves as an asset, only $9 represent net financing that is available to fund new loans.
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Moreover, as noted, the analog to the price of permits is the current setting is the nominal interest rate. This is because when banks want to create money, they are forced to hold non–interest- bearing reserves, and the nominal interest rate represents the opportunity cost of doing so.
Denoting the nominal interest rate by i, one can express the time 2 price level as:
(17) Λ2 = Λ0(1 + i)
RM .
Now suppose a bank wishes to increase its net issuance of real M by one unit at time 0, thereby increasing its real time 2 profits by dΠdM . To do so, it must increase net nominal M by Λ0 units, which requires it to hold ρΛ0/(1−ρ) of nominal reserves. To finance these reserve holdings, it must pay ρiΛ0/(1−ρ) of nominal financing costs at time 2. The real time 2 value of these financing costs is therefore ρiΛ0(1−ρ)Λ2 or, using equation (17),
ρiRM
(1−ρ)(1+i) . For a bank to be indifferent, it must be that these real costs are equal to dΠdM . Thus it follows that the nominal interest rate is given by:
(18) i
(1 + i) =
(1 −ρ) ρRM
dΠ dM
.
EXAMPLE 3. Keep everything the same as in Example 1: f (I) = ψlog(I) + I, g(K) = θlog(K), RB = 1.04; RM = 1.01; ψ = 3.5; θ = 150; λ=1; W =140; and p=0.98. At the social optimum of M∗∗=55.2, we had that dΠdM = 0.0056. With a reserve requirement of ρ = 0.10, if this optimum is implemented with monetary policy, the nominal interest rate is given by i = 5.25%. (Since the nominal rate exceeds the riskless real rate of 1.0%, the implied rate of inflation between time 0 and time 2 is 4.25%.) If we keep all else the same but set RM =1.02, the newoptimum involves M∗∗ = 52.5, which is implemented with a nominal rate of i=1.81%. Intuitively, as the spread between money and bonds shrinks, banks have a weaker desire to create private money. So the nominal interest rate, which is equivalent to the value of a permit for money creation, falls as well.
V. OTHER POLICY TOOLS
V.A. Liquidity Regulation
I have thus far taken the time 0 liquidity stockpile W of the PIs to be exogenous. This does not affect any of the conclusions
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in the foregoing analysis regarding the socially optimal quantity of money, because these conclusions hold for any value of W such that there is a scarcity of PI resources in the bad state at time 1. However, I now pose two related questions about W. First, if the PIs are allowed to choose W optimally, what value will they pick? Second, if the social planner is allowed to choose W, will his choice differ from that of the PIs? In other words, is there a case for regulation of liquidity holdings, in addition to regulation of money creation?
The privately optimal choice of W, denoted by W∗, is deter- mined by the following first-order condition:
(19) pg′(W) + (1 − p)g′(W − M) = RB.
The logic is straightforward. PIs raise W at time 0, paying a gross interest rate of RB.25 With probability p, the good state ensues, and the marginal return on their investment is g′(W). With probability (1 − p), the bad state ensues, and the marginal return on investment is g′(W − M). One interesting feature of this solution is that the more unlikely the bad state, the lower the equilibrium value of W∗, and the deeper the fire-sale discount when the bad state does in fact occur.
To solve for the socially optimal value of W, denoted by W∗∗, we can return to the planner’s Lagrangian from equation (11) and take the first-order condition with respect to W, which yields:
(20) pg′(W) + (1 − p)g′(W − M) = RB + ηP λg′′( ∙ )
RM (g′( ∙ ))2 .
Comparing equations (19) and (20), we can see that the pri- vate and social solutions once again diverge only when ηP > 0, that is, when the collateral constraint binds. Moreover, when this does happen, the additional term in equation (20), ηP λg
′′(∙) RM (g′(∙))2
, is nega- tive, meaning that the planner prefers a lower marginal product of W, or alternatively, a higher level of W. Thus optimal regulation takes the form of a floor on liquidity holdings by the PIs.26
25. The assumption that the PIs’ cost of capital is RB, rather than RM , is tantamount to saying that they are unable to issue any riskless debt. This would be the case if their production technology g(K) were risky, and had some probability of delivering zero output at time 2. However, even if the PIs could issue riskless claims, the rest of the analysis would be little changed, since the return on these claims is already pinned down independent of their quantity. Thus the marginal appeal to the banks of issuing short-term debt against their long-term assets is unaffected if the PIs do some additional riskless financing on the side.
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This result connects to Farhi, Golosov, and Tsyvinski (2009), who also develop a rationale for liquidity regulation. However, the mechanism in FGT is quite different. Following Diamond and Dybvig (1983), Jacklin (1987), Bhattacharya and Gale (1987), and Allen and Gale (2004), they model banks as providers of insurance to consumers with unpredictable liquidity needs. As this litera- ture has shown, incentive-compatible insurance can be frustrated by the existence of securities markets, since “late” consumers may be tempted to mimic “early” consumers by withdrawing their money from the bank prematurely and reinvesting it at the market rate of interest. The insight of FGT is that liquidity requirements can be used to depress the security market rate, thereby reducing the temptation for late consumers to withdraw early. By contrast, in my model, real rates are pinned down by the linear preferences of households and thus unaffected by liquidity requirements. Instead, the rationale for a liquidity requirement reflects a desire to reduce the equilibrium fire-sale discount.27
Although liquidity requirements arise naturally in my frame- work, there are a couple of caveats. First, the liquidity require- ments envisioned by the theory may be difficult to enforce. To implement them efficiently, they have to be imposed on PIs at time 0, in proportion to the scale of each PI’s time 1 investment opportunities. But a regulator may not know at time 0 what the distribution of time 1 projects across PIs looks like. By contrast, the monetary regulation does not face this enforcement problem, since short-term debt issuance is contemporaneously observable at time 0.
Second, in the limited set of numerical experiments that I have tried, the planner’s utility gain from imposing liquidity regulation turns out to be much smaller than that from regulating the creation of private money. Combined with the enforcement problem, this helps explain why the primary focus of the analysis
26. As emphasized, liquidity requirements can never obviate the need for regulation of money creation. One way to show this formally is to note that according to equations (19) and (20), liquidity regulation is only ever worth using when the collateral constraint binds in equilibrium. However, as we have seen, when the collateral constraint binds, it is always desirable to regulate money creation.
27. At a more abstract level, the two models are similar in the following sense. In both models there is an additional constraint beyond the budget constraint: an incentive compatibility constraint in FGT, and a collateral constraint in my model. Moreover, in both models, a market price (the interest rate, or the fire-sale price) enters into the constraint; this is what motivates the planner to intervene, in an effort to change the market price and thereby relax the constraint.
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in this article has been on the latter. The following example is illustrative of the magnitudes that arise.
EXAMPLE 4. Keep everything the same as in Example 1, except allow W to be chosen endogenously: f (I) = ψlog(I) + I, g(K) = θlog(K), RB = 1.04; RM = 1.01; ψ = 3.5; θ= 150; λ= 1; and p = 0.98. The PIs’ optimal choice of W is given by W∗ = 146.31, whereas the social optimum is given by W∗∗ = 147.04. Compared to a benchmark case with no regulation at all, the following regulatory configurations produce these increases in the plan- ner’s utility: (i) regulation only of money creation: +0.0148; (ii) regulation of both money creation and liquidity: +0.0167; and (iii) regulation of just liquidity: +0.0014. Thus in this example, the benefit of liquidity regulation is approximately one-tenth that which comes from regulating money creation.
V.B. Deposit Insurance and Lender of Last Resort
In the baseline version of the model, the only way for banks to pay off their short-term creditors in the crisis state is by fire- selling their assets, and the only role for policy is to control the amount of short-term debt that is created ex ante. An alternative approach would be for the government totry tostem the amount of socially costly fire sales that occur for a given amount of short-term bank debt. This could be done either with either deposit insurance or a lender-of-last-resort policy.
Unlike in the classic framework of Diamond and Dybvig (1983), such policies are not costless to the government in equi- librium, because here, in the crisis state, there is a probability (1−q) that the banks’ assets will turn out to be entirely worthless. So there is always a chance that taxpayers will be left on the hook. If taxpayer-financed bailouts create deadweight losses, the overall optimum set of policies may have the realistic feature that: (1) some fraction of banks’ money-like claims are insured by the government; (2) the remainder are uninsured, and hence still subject to fire-sale risk; and (3) as before, it makes sense for the regulator to control the total quantity of bank-created money.
To see this explicitly, consider a case where the deadweight costs of taxation take the following form: there is no cost to raising any amount less than L to pay for a bailout, but it is infinitely costly to raise anything more than L. It follows that the amount of government-insured money that can be created, MI, is bounded by MI ≤ L, and it will in fact always be optimal to set MI = L.
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Note, too, that if the government offers insurance on some amount of bank deposits, it will have to put in place a rule to prevent banks from selling all of their assets in a crisis state to satisfy the demands of uninsured depositors; otherwise banks will create just as much uninsured money as before, and the deposit insurer will always be left holding an empty shell in the crisis state. A simple version of such a rule—which can effectively be thought of as a ban on fraudulent conveyance—is a requirement that the fraction of assets sold in a crisis, Δ, not exceed the relative proportion of uninsured deposits. Thus the requirement that goes along with insurance is that Δ≤ M
U
MU +MI , where MU is the quantity
of uninsured money created by the bank. It follows that the total amount of money—insured plus
uninsured—that can be created must satisfy the same collateral constraint as before: M = MU + MI ≤ kλI. The only thing that is changed is the determination of the fire-sale discount k. Since insured depositors are protected and do not need to demand repayment at time 1, only uninsured deposits give rise to fire sales. Thus k is now given by:
(21) 1 k
= g′(W − MU ) = g′(W − M + L).
In other words, the outcome in a world with limited deposit insurance is equivalent to that in a world with no deposit insurance, but where the wealth of the PIs is augmented from W to (W + L). A given amount of total money creation now causes less fire-sale damage, and as a result, more money can be created in equilibrium.
Equation (21) also makes clear the close connection between deposit insurance and a lender-of-last-resort function. Given that the government can never put itself in a position to lose more than L, an alternative to deposit insurance would be for it to leave all deposits uninsured but to commit to step in and invest L alongside the PIs in the event of a fire sale. This would have exactly the same effect—it would reduce the fire-sale discount per equation (21) and thereby allow for more total money creation.
The bottom line is that one can add deposit insurance to the model in such a way as to make it more realistic, without changing any of its qualitative properties. The optimal policy mix will involve limited use of deposit insurance or, equivalently, limited use of a lender-of-last-resort function. Banks will continue to issue uninsured money-like claims alongside insured deposits,
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and hence will continue to create some degree of fire-sale risk. Thus, as before, there will continue to be a motive for regulating the creation of these uninsured short-term claims.
V.C. Regulating the Shadow Banking System
The model also assumes that all private money is manu- factured by commercial banks that are subject to reserve re- quirements. Hence, private money creation can be completely controlled by conventional open market operations. Though this may be an adequate representation of an earlier period in history, it omits an important form of money creation in the modern econ- omy. As Gorton and Metrick (2011) and Gorton (2010) emphasize, private money—in precisely the sense meant here—is alsocreated by the unregulated shadow banking system, via the large volume of short-term claims that are collateralized by securitized loan pools of one form or another.
This observation suggests that commercial banks and shadow banks should be regulated in a symmetric fashion. According to the logic of the model, the ideal way to do this would be to broaden the reach of reserve requirements, so that the cap-and-trade regime covers all the short-term liabilities of both commercial banks and shadow banks. If, due to some political constraint outside the model, the liabilities of shadow banks cannot be subjected to reserve requirements, an alternative approach might be to impose a regime of “haircut” regulation. For example, the central bank could specify the maximum fraction of short-term financing that could be issued against a given amount of collateralizable assets. Moreover, just as the optimal quantity of bank-created money M∗∗ varies with economic conditions, optimal haircuts would respond to these conditions as well. The Appendix provides a brief analysis of haircut regulation. It turns out that although such regulation is indeed useful, it is strictly less efficient than direct control of the quantity of privately created money via, for example, the sort of reserve requirements–based mechanism already outlined.
V.D. Government Debt Maturity
As we have seen, the magnitude of the externality associated with private money creation is related to the bond-money spread (RB − RM ): when the spread widens, the wedge between the social and private returns to money creation goes up. Thus an alternative way to moderate the externality would be to compress
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the spread. In the current version of the model this is impossible— given the assumption of linear preferences, the spread is exoge- nously fixed and insensitive to asset supplies.
However, if one changes the model so that the monetary ser- vices enjoyed by households are a concave function of the supply of money—that is, there is diminishing marginal utility of money— then it becomes possible for the government to act on the bond- money spread. For example, since short-term Treasury bills are riskless, they can provide the same monetary services as short- term bank debt. Hence, an increase in the supply of Treasury bills will, in this modified setting, reduce the bond-money spread.
One appeal of dealing with the externality in this fashion is that unlike some other regulatory approaches, it does not invite evasion. For example, if the scope of reserve requirements were broadened, private actors might try to get around limits on their ability to use short-term debt by using various forms of hidden borrowing, for example, by embedding the borrowing in an opaque derivative contract. In contrast, when the relative cost of short- term borrowing goes up—because the market has been saturated with riskless short-term claims—the incentive to create private money is blunted.
In Greenwood, Hanson, and Stein (2010), we use this obser- vation as the point of departure for a normative theory of govern- ment debt maturity. We argue that the government should choose a shorter debt maturity—and in particular, should issue more riskless T-bills—than it otherwise might, in an active effort to crowd out the short-term debt of financial intermediaries. The ar- gument is based on a principle of comparative advantage. On the one hand, tilting its issuance toward short-term debt is not with- out cost for the government, since with stochastic interest rates this increases the variability of future interest payments and ulti- mately disrupts efforts to smooth tax rates over time. On the other hand, short-term government debt, unlike the short-term debt of financial intermediaries, does not create fire-sale risk. To the extent that the fire-sale externality is more costly to the economy at the margin than the disruption of tax smoothing, it can make sense for the government to take on a bigger role in providing the short-term riskless claims that the economy demands.28
28. To the extent that monetary services reflect an ability to transact between time 0 and 1 without threat of adverse selection, the relevant notion of risk is short-horizon risk—that is, the potential for loss between time 0 and time 1. While long-term Treasuries offer certain ultimate payoffs, they are not riskless over short
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Of course, precisely because of tax-smoothing considerations, it will not generally be optimal for the government to tilt so strongly toward short-maturity issuance as to entirely eliminate the bond-money spread in equilibrium. Rather, optimal behavior by the government on this dimension will typically involve leaving the spread only partially compressed. Although government debt maturity may be one helpful tool in addressing the problem of excessive private money creation, it is not a panacea, and it is unlikely to eliminate the usefulness of the other tools.
V.E. Interest on Reserves
I have thus far assumed that the price level is determined outside the central bank, by the fiscal theory mechanism. Though this is a convenient modeling device, it is not an essential piece of the story. An alternative approach, in the New Keynesian spirit, would be to model prices as being anchored by the central bank’s adherence to a “Taylor rule” (Taylor 1993, 1999) which dictates its path for the short-term nominal rate.
However, this raises a potential problem of there being more objectives than tools. If the short-term nominal rate must satisfy a Taylor rule to maintain price stability, how can it also satisfy equation (18), which specifies its optimal value from a regulatory perspective? One way out of this box is via the payment of interest on reserves (IOR), which many central banks around the world have been doing for years, and which the U.S. Federal Reserve first took up in October 2008. As Goodfriend (2002) points out, with IOR, there are two distinct methods for raising short-term nominal rates: by increasing the interest paid on reserve balances, or by draining reserves from the system, thereby increasing their scarcity value. These methods are not equivalent, because only the latter scarcity-based approach increases the effective “reserves tax” paid by banks, which has been the focus of the foregoing analysis.
Building on this observation, Kashyap and Stein (2012) argue that IOR allows the central bank to simultaneously accomplish two goals: (1) set the short-term nominal rate in accordance with a Taylor rule, and (2) implement an optimal regulatory scheme
horizons if interest rates are stochastic. Hence, they can create adverse-selection problems in trade if one party to a transaction has a better ability to forecast changes in rates than the other.
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of the sort described in this article.29 They note that in a regime with IOR, one can decompose the nominal federal funds rate f as follows:
(22) f = rIOR + ySVR,
where rIOR is the level of interest paid on reserves, and the ySVR is the quantity-mediated scarcity value of reserves. The latter term corresponds exactly to the variable i in equation (18), as it reflects the opportunity cost to a bank of holding reserves.
For example, suppose that an analysis of the sort suggested by equation (18) yields the conclusion that for regulatory pur- poses, the optimal value of i (or equivalently, of ySVR) is 2.0%, whereas an application of the Taylor rule implies that the optimal value of f is 5.0%. In this case, the central bank should set rIOR to 3.0%, and then adjust the quantity of reserves in the system until f equilibrates at 5.0%.
VI. A DISTINCTIVE ACCOUNT OF THE MONETARY TRANSMISSION MECHANISM
Much of the discussion has focused on the normative im- plications of the model. But the model is also of interest as a positive account of the monetary transmission mechanism. Three of its properties are particularly noteworthy in this regard. First, monetary policy has real effects even though all prices are per- fectly flexible. Second, monetary policy works entirely through a quantitative effect on bank lending. That is, the real rates on both money and bonds are fixed and independent of the stance of policy; an easing of policy impacts bank lending only because it enables banks to use more of the former, relatively cheaper funding source. This is a pure version of the bank lending channel, and as such helps explain how monetary policy can have important real effects even when it does not move long-term open market interest rates by much, or when firm investment is not very responsive to such open market rates.
Third, the model has the property that the central bank does not lose control of monetary policy when other, nonreservable forms of money are introduced. Consider what happens if there is, in addition to the risky production technology already in
29. See Woodford (2011) for a more complete treatment of these issues in a dynamic New Keynesian model.
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the model, a safe storage technology. Claims to this technology are riskless, and hence circulate as an alternative transactions medium alongside bank-created money, bearing the same gross interest rate of RM . They are also not subject to reserve requirements. (To be more concrete, one can interpret these claims as money market fund deposits backed by Treasury bills.) Even if the volume of these claims is large, nothing in the model changes. All real rates are already pinned down by the linearity of household preferences and are therefore unaffected by the total quantity of money in circulation.
The distinctive feature of the model in this regard is that the central bank’s ability to influence real outcomes derives not from its control over the total quantity of transactions facilitating claims available to households, but from the fact that it is the unique provider of permits that allow banks to issue short-term debt and hence finance themselves more cheaply. Simply put, only central bank–provided reserves can be used to satisfy the reserve requirements that constrain short-term debt issuance by banks. This “permits” aspect of monetary policy is also emphasized in Stein (1998), though the model in that paper differs significantly on other dimensions.30
VII. CONCLUSIONS
The basic message of this article can be summarized as fol- lows. Banks and other financial intermediaries like to fund them- selves with short-term debt. With sufficient collateral backing it, this short-term debt can be made into riskless money, which, because of the transactions services it generates, represents a cheap source of finance for banks. While society benefits from this private money creation, banks’ private incentives lead them to overdo it, since they do not fully internalize the fire-sales costs that are a by-product of their maturity transformation activities. The externality associated with excessive private money creation provides a fundamental rationale for financial stability regula- tion, and arguably, for the existence of central banks.
In a sufficiently simple institutional environment, the ex- ternality can be addressed with conventional monetary policy,
30. In Stein (1998), reserves are effectively permits that allow banks to access the deposit insurance fund. Because banks face an adverse selection problem in raising uninsured finance, an increase in the quantity of reserves can move lending closer to the first-best level.
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complemented by either deposit insurance or a lender-of-last- resort facility. Indeed, this is one interpretation of what central banks have done for much of their history. In a more realistic modern-day setting, where a substantial shadow banking sector exists alongside traditional commercial banks, other tools, such as expanded reserve requirements, or haircut regulation, may also be necessary. If so, central banks should not be reluctant to deploy these tools—to the extent that they do so in an effort to contain excessive private money creation, they can be said to be pursuing one of their traditional core missions in a more comprehensive and effective manner.
APPENDIX
A. A Variant of the Model with Imperfect Pledgeability
As noted in the text, the result that there is no externality in the low M region when m < mmax is dependent on the assumption that when the PIs invest in real projects, they capture all the social surplus associated with these projects. An alternative approach is to assume that the social return to a project financed by a PI is still given by g(K), but that only ϕg(K) can be pledged to the PI. In this case, the equilibrium determination of k in equation (4) is altered so that 1k = ϕg
′(W − M). Equation (7), the bank’s first-order condition with respect to
m, still holds as stated. If the collateral constraint is not binding, so that η = 0, this condition reduces to:
(23) (RB − RM )− (1 − p)zRM = 0.
However, the planner’s first-order condition for m in equation (12) is now modified, because we can no longer substitute 1k =g
′(W−M). Instead, if ηP = 0 this condition can be written as:
(24) (RB − RM )− (1 − p)zRM − (1 − p)(1 −ϕ)g′(W − M)RM = 0.
Thus even in the low spread region where m < mmax and I = IB, there is now a wedge of (1 − p)(1 − ϕ)g′(W − M)RM
between the private and social first-order conditions. This implies that the optimal price of permits will now be strictly positive in this region. Alternatively, in the monetary policy implementation of the optimum, the nominal interest rate will now be strictly positive for all parameter values.
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Another noteworthy feature of this version of the model is that it implies different comparative statics than the baseline model with respect to the ex ante probability of a financial crisis, as captured by (1 − p). Here, if we are in the low-spread region, an increase in (1 − p) increases the wedge, and hence raises the optimal value of the permit price P, or equivalently, the nominal interest rate. By contrast, in the baseline model with perfect pledgeability, equation (14) says that an increase in (1−p) lowers the desired permit price. Intuitively, the difference is that in the baseline version of the model, banks doa better job of internalizing the social costs of fire sales. Indeed, when the risk of a fire sale goes up, banks become sufficiently more cautious about using short- term debt that they become better aligned with the social planner, which in turn implies that there is less need to rein them in by raising permit prices/interest rates. However, with imperfect pledgeability, there is an effect in the opposite direction, because banks tend to underweight the social costs of fire sales even when the collateral constraint is not binding.
B. Haircut Regulation
To see the effects of haircut regulation most transparently, consider the imperfect pledgeability version of the model just described. Suppose that we are in a “shadow banking” economy where all else is the same as before, with one exception: it is impossible to regulate the absolute quantity of privately created money M directly—say, because shadow banks cannot be sub- jected to reserve requirements—but it is possible to impose a cap mcap < mmax on the fraction of investment that is money financed.
It turns out that this form of haircut regulation, though useful, is a second-best means of intervention as compared to controlling the aggregate quantity of money. This is because the social costs of fire sales are a function of M, so this is the item the planner would ideally like to control. Trying to do this indirectly, by picking a value of mcap, will now have the undesired side effect of encouraging shadow banks to raise their investment above the optimal level of IB. (I assume that we are in the low spread region of the parameter space, so that absent haircut regulation, shadow banks would choose I = IB.) Intuitively, haircut regulation always gives shadow banks the option to create more cheap money financing at the margin, as long as they are willing to raise the level of investment.
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This can be seen formally by considering the first-order con- dition with respect to I for a shadow bank facing binding haircut regulation:
(25) dΠ dI
= pf ′(I)+ (1−p)λ−RB + mcap{(RB−RM )−(1−p)zRM}= 0.
It follows that it is impossible to use haircut regulation to im- plement the social optimum described in equation (24). For if equation (24) is satisfied with I = IB, it must be that (RB − RM )− (1−p)zRM = (1−p)(1−φ)g′(W −M)RM > 0. But then for equation (25) to be satisfied, that is, for the shadow bank to be optimizing given the haircut constraint, we require pf ′(I) + (1−p)λ−RB < 0, which means that I > IB.
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- Introduction
- A Model of Private Money Creation
- Households
- Banks
- Patient Investors
- The Bank's Optimization Problem
- Socially Excessive Money Creation: A Role for Regulation
- The Social Planner's Problem
- Understanding the Nature of the Externality
- A ``Cap-and-Trade'' Approach to Bank Liquidity Regulation
- Relationship to Pigouvian Taxation
- implementing the cap-and-trade approach with monetary policy
- Other Policy Tools
- Liquidity Regulation
- Deposit Insurance and Lender of Last Resort
- Regulating the Shadow Banking System
- Government Debt Maturity
- Interest on Reserves
- A Distinctive Account of the Monetary Transmission Mechanism
- Conclusions
- A Variant of the Model with Imperfect Pledgeability
- Haircut Regulation
Monetary-and-financial-stability-Here-to-stay-_2006_Journal-of-Banking-Finance.pdf
Journal of Banking & Finance 30 (2006) 3407–3414
www.elsevier.com/locate/jbf
Monetary and financial stability: Here to stay?
Claudio Borio *
Head of Research and Policy Analysis, Monetary and Economic Department,
Bank for International Settlements, 4002 Basel, Switzerland
Available online 24 July 2006
Abstract
We argue that changes in the monetary and financial regimes over the last twenty years or so have been subtly altering the dynamics of the economy and hence the challenges that monetary and pru- dential authorities face. In particular, the current environment may be more vulnerable to the occa- sional build up of financial imbalances, i.e. over-extensions in (private sector) balance sheets, which herald economic weakness and unwelcome disinflation down the road, as they unwind. As a result, achieving simultaneous monetary and financial stability in a lasting way may call for refinements to current monetary and prudential policy frameworks. These refinements would entail a firmer long- term focus, greater symmetry in policy responses between upswings and downswings, with greater attention to actions during upswings, and closer coordination between monetary and prudential authorities. � 2006 Elsevier B.V. All rights reserved.
JEL classification: E30; E44; E50; G10; G20; G28
Keywords: Monetary stability; Financial stability; Financial imbalances; Prudential policy; Monetary policy
1. Introduction
Today I would like to share with you some personal reflections on the nexus between monetary and financial stability. Specifically, I will address two questions: What is the relationship between monetary and financial stability? How can we achieve the two simul- taneously in a lasting way?
0378-4266/$ - see front matter � 2006 Elsevier B.V. All rights reserved. doi:10.1016/j.jbankfin.2006.06.004
* Tel.: +41 61 280 8436. E-mail address: [email protected]
3408 C. Borio / Journal of Banking & Finance 30 (2006) 3407–3414
My remarks will be based on a line of research carried out with colleagues at the BIS over the last few years. The views expressed, however, should be taken as strictly my own.
This line of work is based on two observations. First, over the last two decades central banks have been extremely successful in conquering inflation, but financial instability has become a major policy concern. Financial crises in both industrial and emerging market countries have resulted in major output losses. Second, throughout modern history the simultaneous achievement of monetary and financial stability has in fact remained rather elusive (Borio and Crockett, 2000; Borio, 2005).
The main conclusion I draw from this work is that we are closer than ever to achieving the goal, but that doing so requires some refinements to current monetary and prudential policy frameworks. These refinements would entail a firmer long-term focus, greater sym- metry in policy responses between upswings and downswings, with greater attention to actions during upswings, and closer coordination between monetary and prudential authorities. The main risk is that the problem could fall through the cracks: each type of authority might well agree with the diagnosis, but put the burden of action on the other. The result would be the failure of policymakers to act.
Given the limited time available, I can do no more than sketch the basic argument and some empirical evidence for it. Moreover, while the literature on these issues is quite vast and growing rapidly, I will just refer to BIS work. For a comprehensive set of references, you should refer to those pieces of work.
2. The thesis
The thesis is that changes in financial and monetary regimes worldwide may have been subtly altering the dynamics of the economy and hence the challenges that monetary and prudential authorities face.
On the one hand, financial liberalisation may have made it more likely that financial fac- tors in general, and booms and busts in credit and asset prices in particular, act as drivers of economic fluctuations. On the other hand, the establishment of a regime yielding low and stable inflation, underpinned by central bank credibility, may have made it less likely that signs of unsustainable economic expansion show up first in rising inflation and more likely that they emerge first as excessive increases in credit and asset prices (the ‘‘paradox of credibility’’).
As a result, the current environment may be more vulnerable to the occasional build up of financial imbalances, ie over-extensions in (private sector) balance sheets. These imbal- ances herald economic weakness and unwelcome disinflation down the road, as they unwind. The unwinding may occur because the boom falters under its own weight or because inflation eventually does emerge and the central bank is forced to tighten.
One can refer to the property of the economy that makes the emergence of financial imbalances more likely as increased ‘‘procyclicality’’ (Borio et al., 2001; BIS, 2001) or, more graphically, increased ‘‘elasticity’’ (Borio and White, 2004).
Let me next say a few words about the role of the financial and monetary regimes, respectively.
Financial liberalisation is undoubtedly critical for a better allocation of resources and long-term growth. The serious costs of financial repression around the world have been well documented.
C. Borio / Journal of Banking & Finance 30 (2006) 3407–3414 3409
But financial liberalisation has also greatly facilitated the access to credit. It has there- fore also increased the scope for perceptions of wealth and risk to drive the economy, more easily supported by external funding.
During booms, self-reinforcing processes can develop. These are characterised by rising asset prices, falling perceptions of risk, loosening external financing constraints and rising output. Financial imbalances arise when, less constrained by this looser anchor, the pro- cesses go too far. As a result, the financial system does not build up sufficient cushions, sowing the seeds for a subsequent bust.
Excessive procyclicality can arise because of two ‘‘gaps’’. They relate, respectively, to risk perceptions and incentives.
The risk perceptions gap refers to the fact that economic agents seem to be better at measuring the cross-sectional than the time-dimension of risk, especially that of system- wide risk (Borio et al., 2001 and Lowe, 2002). Market indicators of risk, such as p/e ratios and credit spreads, are comparatively low close to the peak of the financial cycle. And this is precisely when, at least in hindsight, risk is highest. Markets behave as if risk fell in booms and rose in recessions. But it may be better to think of risk as rising in booms, if and when financial imbalances build up, and as materialising in recessions, as they unwind. The length of the horizon over which risk is assessed is key here.
The incentives gap refers to the fact that actions that may be rational, or indeed com- pelling, at the level of individual agents or institutions need not result in desirable aggre- gate outcomes. Familiar notions here include prisoner’s dilemmas, coordination failures, and herding. For instance, is it reasonable to expect a bank manager to trade off a sure loss of market share in a boom against the distant hope of regaining it in a future potential slump? Here again, short horizons are key. And they may in turn result from the contrac- tual mechanisms designed to overcome ‘‘asymmetric information’’ obstacles, which may thus have unintended consequences. The frequent monitoring of performance based on short-term benchmarks is one such example.
What about the role of the monetary regime? It is well know that high and variable inflation can distort the allocation of resources and generate financial instability. Both a priori reasoning and past experience attest to that.
But financial imbalances can also develop in a low inflation environment. For one, the overly optimistic expectations that tend to go hand-in-hand with unsustainable booms are more likely to be triggered by favourable supply-side developments, which naturally put downward pressure on prices. Obvious such examples include economic globalisation and productivity gains due to technological advances, quite prominent over the last decade or so. More subtly, though, the credibility of policymakers’ commitment to price stability, by anchoring expectations and hence inducing greater stickiness in price and wages, can delay the inflationary pressures normally associated with the unsustainable expansion of aggregate demand. And low inflation, by obviating the need to tighten mon- etary policy, can also remove a key constraint on the development of the imbalances.
3. The evidence
Three pieces of evidence are consistent with the basic hypothesis. First, especially since financial liberalisation in the early 1980s, we have seen larger
booms and busts in credit and asset prices. These have often been followed by outright
3410 C. Borio / Journal of Banking & Finance 30 (2006) 3407–3414
financial crises or at least serious financial strains with material consequences for the real economy (Graph 1).
Second, more formal empirical evidence suggests that indicators of financial imbalances can help to predict banking distress, economic weakness and disinflation over a 3–5 year horizon (Borio and Lowe, 2002a,b, 2004 and Table 1). Importantly, the indicators are based on real-time measures of joint excessive asset price increases and credit growth. The proxies are intended to measure the coexistence of asset price misalignments with a limited capacity of the system to absorb the asset price reversal. Misalignments are simply captured by deviations of equity and possibly exchange rates from trend, the absorption capacity of the system by the ratio of private sector debt to GDP. Crucially, these indica- tors are based only on ex ante information, ie on information that is available at the time
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Real aggregate asset prices (1980 = 100; lhs) Total private credit/GDP (ratio; rhs)
Large medium-term swings in asset prices and credit
G10+1 United States Japan
United Kingdom France Australia
Sweden Norway Finland
1 GDP-weighted average of the G10 countries plus Australia, Denmark, Finland, Norway and Spain; weights based on 2000 GDP and PPP exchange rates.
Sources: Private real estate associations; national data; BIS calculations; Borio and White (2004).
Graph 1.
Table 1 Financial imbalancesa as predictors of banking distress, output weakness and disinflation
Horizon (years)d Banking distressb Industrialised countriesc
Industrialised countries Emerging market countries Credit gap (4) and equity gap (60)
Credit gap (4), equity gap (60) and output gap (2)
Credit (4) and asset price (40)
Credit (4) and (asset price (40) or exchange rate (13))
Horizon (years)4
Banking distress Horizon (years)
Output weakness
Disinflation
Noise/signal % crises predicted
Noise/signal % crises predicted
Noise/signal % crises predicted
Conditional probabilitiese
1 0.09 50 0.16 67 3 .06 47 2 55 36 (1.06) (�1.07)
1, 2 0.06 56 0.12 71 3, 4 .02 47 3 99** 55 (2.91) (.31)
1, 2, 3 0.04 63 0.09 75 3, 4, 5 .02 73 4 1.00f 92*
– (2.38)
Sources: Borio and Lowe (2002b) and Borio and Lowe (2004). a The proxies for financial imbalances are calculated based on deviations of the corresponding variables from ex ante (one-sided) recursive Hodrick-Prescott filter
trends (‘‘gaps’’, with percentage points in brackets). The value of lambda is 1600 (for annual data) and 400,000 (for quarterly data). Depending on the exercise, the variables used include the ratio of private sector credit to GDP, inflation-adjusted equity prices, the real effective exchange rate and the output gap (conventionally measured, with lambda equal to 1600 in quarterly estimation).
b Annual data. c Quarterly data. d A signal is correct if a banking crisis takes place in any of the corresponding years ahead included in the horizon. e Conditional probabilities of output weakness (ex ante output gap smaller than minus 1%) and of a decline in inflation (average for the year) in the given year
ahead. The corresponding unconditional probabilities are 39% (output weakness) and 50% (decline in inflation), respectively. Z-statistics for the probit regressions in brackets. Two and one asterisks correspond to statistical significance at the 1% and 5% level, respectively.
f Conditional probability calculated by counting the frequency of events; the econometric routine does not converge. If the output gap is excluded from the indicator, the corresponding figures for the combined credit and equity gap are 41 (.50), 66** (5.54) and 75** (7.00) for the horizon in year 2, 3 and 4 ahead respectively.
C .
B o
rio /
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u rn
a l
o f
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n k
in g
& F
in a
n c e
3 0
( 2
0 0
6 )
3 4
0 7
– 3
4 1
4 3
4 1
1
3412 C. Borio / Journal of Banking & Finance 30 (2006) 3407–3414
the assessments of vulnerabilities are made. In particular, the trends are calculated only up to that point.
Finally, financial imbalances have also occurred during periods of low and stable infla- tion (Graph 2). In the distant past, well-known examples include the financial crises dur- ing the classical and exchange gold standards. More recently, cases in point include the experience in Japan and several countries in East Asia and, without a full-blown crisis following, in the United States. Arguably, at present, developments in China as well as in housing markets in several countries around the world exhibit similar characteristics (Borio and McGuire, 2004; BIS, 2005).
Upper panel (indices; log scales)1 : Consumer prices (lhs)2
Credit/GDP (lhs)
Share prices (rhs)3
Property prices (rhs)4
Lower panel (in percentages; rhs): Annual change in consumer prices
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Low and stable inflation and financial instability: selected episodes
United States – 1920s Japan – 1980s / 1990s
Australia – 1880s Korea – 1980s / 1990s
1 Base year: for the United States, 1923; for Japan, 1980; for Australia, 1880; for Korea, 1987. 2 For Australia, GDP deflator. 3 For the United States, S&P 500; for Japan, Nikkei 225; for Australia, All Ordinaries. 4 For the United States, Chicago land value; for Japan, Tokyo commercial land prices; for Australia, Melbourne capital value of rateable property.
Graph 2. Sources: For property prices: Tokyo National Land Agency and local governments; Chicago, Hoyt (1933); Melbourne, Kent and D’Arcy (2001); otherwise, Taylor ‘‘Global Financial Data’’ (database) and national
C. Borio / Journal of Banking & Finance 30 (2006) 3407–3414 3413
4. Policy implications
This hypothesis, if accepted, has significant implications for prudential and monetary policies (Borio and White, 2004 and Borio, 2005).
As regards prudential policy, it is essential to strengthen the macro-prudential orienta- tion of the frameworks (Borio, 2003). This means taking further the shift in the orientation of present frameworks away from a focus on individual institutions towards one on the system as a whole. And it means addressing more explicitly the endogeneity of risk with respect to the collective behaviour of institutions. This is the endogeneity of risk that arises largely from the incentives gap identified above, whereby extension can result in over- extension and retrenchment in over-retrenchment.
What does this mean more concretely? First, it means encouraging the build up of cushions in good times so that they can be
run down, up to a point, in bad times. Unless they are run down, they cannot act as cush- ions in the first place; so they need to be sufficiently high to start with. This policy would strengthen individual institutions and the system as a whole. Moreover, by leaning against the procyclical forces of the economy, it could limit the size of financial imbalances and hence the risk of subsequent financial instability.
Second, it means improving the measurement of system-wide risks. This would help to calibrate prudential instruments and improve firms’ own risk management (Tarashev, 2005). Better measurement could be based on a broader assessment of vulnerabilities. It would be guided by the type of considerations behind the indicators developed above and complemented by macro-stress testing and a large dose of judgement. Close cooper- ation of prudential authorities with central banks would be needed. After all, central banks have a comparative advantage in this area, given their long-standing expertise in assessing the links between the macro-economy and the financial system. Despite several efforts made recently in national and international fora, not least at the BIS, work is still very much in its infancy (BIS, 2005).
As regards monetary policy, it is essential that the framework allows enough room for policy to lean against the build up of imbalances even if near-term inflation pressures remain subdued. This would limit the risk of a bigger crash later on, with serious conse- quences for the real economy and also for inflation. Importantly, with inflation low to start with, one should not underestimate the twin risks of unwelcome deflation and of hit- ting the zero lower bound for policy interest rates.
Gaining this flexibility implies two policy refinements. The first is lengthening the policy horizon beyond the one-to-two years typical of some inflation targeting regimes. The cor- responding cumulative processes through which imbalances build up and unfold take con- siderable time. The second is paying more attention to the balance of risks to the outlook. The timing of the unwinding of the imbalances is highly uncertain. And given the obvious forecasting difficulties, the longer horizon should primarily be seen as a device to assess the balance of risks facing the economy in a more meaningful and structured way. Note that, in terms of communication, it may be very hard to explain such a ‘‘deviation’’ from stan- dard strategies.
So, if this thesis is accepted, what do we need to do in order to make further progress? I would highlight three needs. First, we need more analytical work on the relationship between financial imbalances, the real economy and inflation. Second, we need more empirical work on the identification of imbalances. Finally, and above all, we need more
3414 C. Borio / Journal of Banking & Finance 30 (2006) 3407–3414
educational efforts to explain how such policies are consistent with securing price and financial stability on a sustainable basis.
This would help to overcome the reluctance of the two sets of authorities. Prudential authorities may well agree with the diagnosis. But seeing the problems as having a macro-economic origin, they would naturally prefer to leave it to the monetary policymak- ers to respond. Likewise, monetary authorities may well agree with the hypothesis. But seeing the problems as concerning primarily financial instability, they would naturally pre- fer to leave it to the prudential authorities to react. But then, who would take action in the end?
References
Bank for International Settlements, 2001. Cycles and the financial system, BIS 71st Annual Report, June, pp. 123–141 (Chapter VII).
Bank for International Settlements, 2005. BIS 75th Annual Report, June. Borio, C., 2003. Towards a macro-prudential framework for financial supervision and regulation? CESifo
Economic Studies 49 (2/2003), 181–216. Also available as BIS Working Papers, no 128, February. Borio, C., 2005. The search for the elusive twin goals of monetary and financial stability, keynote lecture at the
IGIDR Sixth Annual Conference on Money and Finance in the Indian Economy, 25–27 March 2004. An abridged version is available as National Institute Economic Review 192 (1), 84–101. April.
Borio, C., Crockett, A., 2000. In search of anchors for financial and monetary stability. Greek Economic Review 20 (2), 1–14. Autumn.
Borio, C., Lowe, P., 2002a. Asset prices, financial and monetary stability: exploring the nexus, paper presented at the BIS Conference on Changes in risk through time: measurement and policy options. BIS Working Papers (114), July.
Borio, C., Lowe, P., 2002b. Assessing the risk of banking crises. BIS Quarterly Review (December), 43–54. Borio, C., Lowe, P., 2004. Securing sustainable price stability: should credit come back from the wilderness?’’.
BIS Working Papers (157), July. Borio, C., McGuire, P., 2004. Twin peaks in equity and housing prices? BIS Quarterly Review (March), 79–93. Borio, C., White, W., 2004. Whither monetary and financial stability? The implications of evolving policy
regimes, in Monetary Policy and Uncertainty: Adapting to a Changing Economy, a symposium sponsored by the Federal Reserve Bank of Kansas City, 28-30 August 2003, Jackson Hole, pp. 131–211. Also available as BIS Working Papers, no 147, February.
Borio, C., Furfine, C., Lowe, P., 2001. Procyclicality of the financial system and financial stability: issues and policy options, in Marrying the macro- and micro-prudential dimensions of financial stability. BIS Papers (1), 1–57, March.
Hoyt, H., 1933. One hundred years of land values in Chicago. The University of Chicago Press, Chicago, Illinois. Kent, C., D’Arcy, P.D., 2001. Cyclical prudence—credit cycles in Australia, in Marrying the Macro and Micro-
prudential Dimensions of Financial Stability, BIS Papers, No. 1, pp. 58–90. Lowe, P., 2002. Credit risk measurement and procyclicality. BIS Working Papers (116), September. Tarashev, N., 2005. An empirical evaluation of structural credit risk models. BIS Working Papers (179), July.
- Monetary and financial stability: Here to stay?
- Introduction
- The thesis
- The evidence
- Policy implications
- References
Monetary-and-financial-stability-in-the-euro-area-Pro-cyclicality-versus-trade-off_2009_Journal-of-International-Financial-Markets-Institutions-and-Mo.pdf
Int. Fin. Markets, Inst. and Money 19 (2009) 662–674
Contents lists available at ScienceDirect
Journal of International Financial Markets, Institutions & Money
j o u r n a l h o m e p a g e : w w w . e l s e v i e r . c o m / l o c a t e / i n t f i n
Monetary and financial stability in the euro area: Pro-cyclicality versus trade-off�
Brigitte Granville, Sushanta Mallick ∗
Centre for Globalization Research (CGR), School of Business and Management, Queen Mary, University of London, Mile End Road, London E1 4NS, UK
a r t i c l e i n f o
Article history: Received 20 February 2008 Received in revised form 6 October 2008 Accepted 21 November 2008 Available online 3 December 2008
JEL classification: E30 E44 E50 G10
Keywords: Monetary stability Financial stability Monetary policy EMU VAR sign restriction
a b s t r a c t
This paper investigates the nexus between monetary stability and financial stability. We examine, in the experience of EMU between 1994 and 2008, first, the response of the term structure of interest rates, share prices, exchange rates, property price inflation and the deposit–loan ratio of the banking sector (our proxies for financial stability) to changes in the consumer price level and ECB policy rate (our proxies for monetary stability); second, whether and to what extent lower inflation has caused share price stability and how ECB policy rate has reacted to inflation. Using a sign-restriction- based VAR approach, we find that there is a pro-cyclical relationship between monetary and financial stability in the long-run. With a positive inflation shock, we find on average a 2% estimated decline in share prices. This suggests that the interest rate instrument used for inflation targeting is conducive to financial stability.
© 2008 Elsevier B.V. All rights reserved.
1. Introduction
Given the strong growth in financial markets and instances of financial fragility over the last 10 years, this paper investigates the nexus between monetary and financial stability. While mone- tary stability seems to be less a source of worry than in previous decades, financial stability is an
� We are grateful to an anonymous referee of this journal for the constructive comments on an earlier version of this paper, to Mariusz Jarmuzek for his help on providing us with house price data and to the participants of the European Economics and Finance Society Annual Conference (Prague, Czech Republic, 22–25 May 2008) and Southern Economic Association Annual Conference (Washington, DC, USA, 20–23 November 2008).
∗ Corresponding author. Tel.: +44 20 7882 7447; fax: +44 20 7882 3615. E-mail address: [email protected] (S. Mallick).
1042-4431/$ – see front matter © 2008 Elsevier B.V. All rights reserved. doi:10.1016/j.intfin.2008.11.002
B. Granville, S. Mallick / Int. Fin. Markets, Inst. and Money 19 (2009) 662–674 663
increasing concern of central bankers (De Graeve et al., 2007). A key challenge therefore for cen- tral banks is to maintain monetary and financial stability simultaneously. For Borio and Lowe (2002) and Borio et al. (2003), the achievement of low inflation has created a “new environment”, in the context of which the relation between monetary stability and financial stability has to be reconsid- ered. The success in controlling inflation, underpinning and enhancing central bank credibility at the same time, can conceal imbalances that ultimately lead to higher asset price volatility with serious macroeconomic consequences. Borio (2006) refers to this as a “paradox of credibility.” In other words, policymakers’ decisions to manage liquidity can result in unsuccessful monetary policy. For example, decreasing interest rates to increase liquidity can increase inflation—an example of the “paradox of credibility”.
The concept of financial stability is relatively new and there is no widely accepted definition or model or analytical framework for assessing the stability of the financial system.1 Mishkin (1999) for instance defines financial stability in terms of its opposite which occurs “when shocks to the finan- cial system interfere with information flows so that the financial system can no longer do its job of channelling funds to those with productive investment opportunities”.2 De Graeve et al. (2007) define it as “a bank’s probability of distress according to the supervisor’s definition of problem banks used for supervisory policy” and they find the existence of a trade-off between monetary and financial sta- bility, suggesting that an unexpected tightening of monetary policy increases the mean probability of distress.3
In this paper, financial stability is defined in terms of changes in share prices, interest rate spreads, the nominal effective exchange rate, house price inflation, and bank deposit–loan ratio. We also examine the effect of all these financial variables on the real sector, by including in the empirical model both real GDP and a composite leading indicator. Public policy conducted by a central bank and a financial regulator affects financial stability at both the microeconomic and macroeconomic levels. At the microeconomic level, appropriate regulation helps reduce the risk of financial crisis; lender-of-last-resort and emergency liquidity measures help contain a crisis; and debt resolution mechanisms assist crisis resolution, allowing financial traffic to resume. At the macroeconomic level, the avoidance of policy shocks and the containment of real shocks are important for avoiding sit- uations where the private sector expectations underlying financial structures are disappointed.4 As regards the euro area, the European Central Bank (ECB) has independent powers to maintain price stability, but prudential control and financial stability responsibilities, including the lender-of-last- resort role, remain in the hands of national authorities.5 The ECB can only act in an advisory and co-ordinating capacity in the prudential supervision of banks, and promote the smooth operation of payment systems in EMU. The current system of “institutional balance” based on overlapping jurisdic- tions means that the regulatory and supervisory financial framework of the euro area is triggering a broad debate on its adequacy to ensure financial stability (Kahn and Santos, 2002; Alesina and Perotti, 2004).
Given the long time lags of monetary policy shocks on the real sector, various authors have examined the initial impacts on financial variables such as longer-term interest rates, share prices and foreign exchange rates. For example, Cook and Hahn (1989), Kuttner (2001), Rudebusch (1995) have investi- gated the impact of monetary shocks on the term structure of interest rates, Bernanke and Kuttner (2005) on share prices in the US, and Honda and Kuroki (2006) on both term structure and share prices in Japan. All of them find that these initial impacts are significant; though softened on occasion by prior financial markets anticipation.
In our paper, against the background of this evidence that monetary policy oriented towards price stability promotes financial stability over time, we examine the experience of the twelve EMU countries
1 See Houben et al. (2004), Allen and Wood (2006), Goodhart (2006) and Poloz (2006) for a discussion and a review of the literature on financial stability. Models on financial fragility include, for instance, Goodhart et al. (2006).
2 Mishkin (1999): 6. 3 De Graeve et al. (2007): 3. 4 The institutional structure of financial markets is the concern of a large literature as for instance Gertler (1988) and Bernanke
et al. (1998). 5 See Papademos (2006) for details on the strategies used by the ECB to maintain price stability.
664 B. Granville, S. Mallick / Int. Fin. Markets, Inst. and Money 19 (2009) 662–674
between 1994:Q1 and 2008:Q2. The question is whether low and stable inflation has been associated with financial stability characterized in terms of changes in share prices, interest rates and the nominal effective exchange rate being minimised. First, we establish whether there is a direct link between inflation and asset prices by estimating the response of the term structure of interest rates, share prices, the nominal effective exchange rate (NEER), house price inflation and the bank deposit–loan ratio (our proxies for financial stability) to changes in the price level (our proxy for monetary stability). Secondly, we investigate whether and to what extent changes in asset prices (meaning share prices, interest rate spreads, NEER, and house price inflation) have been caused by inflation shocks and – extending this analysis – policy responses through the ECB policy rate. With a negative inflation shock, we find that there is a pro-cyclical relationship between monetary stability and share-market indices, even in the long-run when the shock dies out. Given the mandate of the ECB to promote monetary stability using the interest rate instrument, we subject the ECB policy rule to the same analysis—namely to what extent the policy rate reacts to changes in inflation and thus affect share prices, house price inflation and future business expectations reflected in the composite leading indicator. We find that the paradox of credibility, which is the idea that successful monetary policy geared to price stability and reducing inflation then causes strong asset price growth, even bubbles, does not seem to hold. As inflation could cause financial instability, policies designed to promote price stability as seen in recent years can promote financial stability in the euro area. In Section 2, we put together a simple framework linking monetary and financial stability. In Section 3, we discuss our data and the way we carry out our empirical estimates of the impact of monetary stability on the financial variables. In Section 4, we summarize our findings.
2. An analytical setting
Our main objective is to investigate how consumer price changes affect first, the term structure of interest rates and second, share prices and NEER. We use the following analytical setting to discuss the linkages between these financial variables and the macro-economy. The framework is in line with a New Keynesian model consisting of a Phillips curve for the supply side and an IS curve for the demand side.
We derive a theoretical formulation for the relationship of inflation with financial variables in an open economy by using dynamic aggregate supply and aggregate demand equations as follows:
�t = �t−i + ˇyt + ε� (AS-curve) yt = ı(ilt − ist ) + �et + �st + εd (AD-curve)
where � is inflation, y is output gap, il is long-term nominal interest rate, and is is short-term nominal interest rate, e is nominal exchange rate, and s is share price index, ε� and εd are sup- ply and demand shocks, respectively. The first equation represents an aggregate supply curve (AS), which is the Phillips curve equation. It assumes that inflation depends on its past level, the output gap and an exogenous supply shock. The second equation is an aggregate demand curve (AD). AD depends on both long-term and short-term interest rates, and share prices and nominal exchange rates. As it is important to account for the role of asset prices in aggregate demand equations to capture any business cycle effect, we consider the movements in equity prices in the demand equation which is in part motivated by a Tobin’s q type of justification in the sense that changes in future profitability of capital would cause share prices to change thus leading to an aggregate demand shock. Substituting AD in AS, we solve for nominal interest rate spread (or term structure) as follows:
ilt − ist = 1
ˇı (�t − �t−i) −
�
ı et −
�
ı st −
( 1
ˇı ε� +
1 ı
εd
) (Term structure)
The term structure equation suggests that the spread between the long-term and the short-term interest rate is primarily driven by actual inflation and its unexpected shocks, as well as by share prices and the nominal effective exchange rate. We calculate the spread as a variable to take into account both the short-term and long-term interest rates together, as opposed to taking them separately. The
B. Granville, S. Mallick / Int. Fin. Markets, Inst. and Money 19 (2009) 662–674 665
Fig. 1. Monetary policy response to a house price shock.
spread helps us to consider the general assumption that central banks smooth short-term interest rate changes to enhance the stability of financial markets and that long-term interest rates could reflect the effect of shocks from other financial markets as in Laopodis (2004).
Similarly, the equation for share prices can be derived to examine the impact of inflation shocks as follows:
st = 1
ˇ� (�t − �t−i) −
ı
� ı �
(ilt − ist ) − �� et − (
1 ˇ�
ε� + 1� εd )
(Share price equation)
As our aim is to look at the impact of inflation shocks (or policy rate) on interest rate spreads, share prices and nominal effective exchange rate, we have derived the above equations. In the same manner, an equation for the impact of inflation shocks on the exchange rate can also be derived as follows:
et = 1
ˇ� (�t − �t−i) −
ı
� (ilt − ist ) −
�
� st −
( 1
ˇ� ε� +
1 �
εd
) (NEER equation)
Besides the above financial variables, house price movements are also important to monitor, as they are likely to move in a pro-cyclical direction. In Fig. 1, we illustrate the linkage between housing market and monetary policy. The upward sloping monetary policy (MP) line reflects the reality that a central bank is more likely to change interest rate depending on inflation (�) in the economy driven by aggregate demand; cutting the rate when there is low inflation and raising it when there is high inflation.6 As there is limited supply of housing and given the high cost of expansion, housing supply is insensitive to changes in price, and any change in demand for housing (HD) will get reflected in changes in house prices (HPI), which in turn can influence overall inflation and thus changes in interest rate policy.
Inflation may increase because of a supply shock (e.g. oil prices) or because of a demand shock (e.g. monetary policy). From a theoretical perspective, an inflation shock that results from a supply disturbance can have different effect than an inflation shock that results from a demand disturbance. To uncover whether a shock in inflation is due to monetary policy, we include ECB policy rate as a proxy in the second part of our empirical analysis in order to capture interest rate response to inflation, which could contribute to changes in asset prices. In other words, the extent to which monetary stability (a negative inflation shock) contributes to changes in financial variables (interest rate spread, share prices, and property prices) is the subject matter of this paper.
6 See Romer (2000) for the rationale underlying an upward sloping MP curve, which captures the actions of a central bank more realistically.
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3. Empirical analysis
3.1. Data
Given the empirical focus, which is to test the nexus between monetary and financial stability, we need to identify different monetary and financial variables in line with the discussion in the previous section. We intend to establish whether the linkage between monetary and financial sta- bility is pro-cyclical or not; and uncover empirically the response of monetary policy as asset prices (equity and property) change. To answer the endogeneity or exogeneity question, we consider the four variables associated in the above reduced form equations in the empirical exercise. We use F-tests to indicate whether we can consider inflation as exogenous. If none of the other variables are significant in explaining inflation, inflation can be considered as exogenous and hence shocks in inflation can be considered as monetary shocks and the dynamic response of other variables can be examined.7
The data frequency is quarterly spanning the period from 1994:Q1 to 2008:Q2. The dataset was ini- tially compiled from the euro area business cycle network (www.eabcn.org), but subsequently updated from the original sources, along with the nominal effective exchange rate and the composite leading indicator, which have been taken from Datastream. The euro area (changing composition) equity index – the Dow Jones Euro Stoxx Broad stock exchange index – is provided by the ECB. The euro area har- monised index of consumer prices (HICP) overall monthly index is taken from Eurostat. The euro area 10-year Government Benchmark bond yield and Money Market 3-month Euribor (Euro Interbank Offered Rate) come from the ECB. The residential property price inflation series have been compiled from ECB at a bi-annual frequency, and they are interpolated to get the quarterly series. Residential property inflation is only available until end-2007, at a bi-annual rate, but we have interpolated the data to have quarterly observations and extrapolated for the first half of 2008 to have a sample until June 2008.8
We have used the Bundesbank discount rate for the period preceding 1999 when the ECB interest rate became available. We have used NEER as a proxy for foreign exchange market, because the euro exchange rate is only available since 1999. Besides, as NEER is likely to determine changes in the current account position – a surplus encouraging people to hold foreign assets and a deficit leading to reduce foreign asset holdings – including this variable can reflect the extent of international transactions.
Besides the nominal interest term spread as a measure of liquidity, the bank deposit–loan ratio can also be considered as a measure of liquidity conditions. Monetary stability can result in lower interest rates which stimulate loan supply, thereby reducing the bank deposit–loan ratio and increasing the likelihood of distress in financial markets. So we include the deposit–loan ratio (DLR) among the set of financial variables. The turmoil in global financial markets triggered by the US sub-prime mortgage crisis underlines the importance of such financial variables, as liquidity crises may spill over to other macroeconomic variables. Data on banking institutions’ demand deposits and loans to households are compiled from Datastream, as these two series are available for the sample period considered in this paper.
We checked for possible breaks in the dataset using the Zivot–Andrews structural break test. All variables are found to be non-stationary with 1999 as the most common break point (introduction of the euro) across different series (see Appendix A). In this paper, however, we adopt Uhlig methodology (described below) which is robust to non-stationarity of series including breaks, consequently we do not include any dummy variable in the VAR.
We define our variables as follows: IRS—interest rate spread between long-term and short-term interest rates for the euro-area; LSHP—log of share price for the euro area stock markets; LNER—log of nominal effective exchange rate; INF—CPI inflation for the euro area; RPP—residential property price inflation; RGDP—real GDP for the euro area; LIND—composite leading indicator for the euro area.
7 Although the variables included in the VAR do not make inflation an endogenous variable statistically (except as regards its own lagged values), in reality inflation is an endogenous variable that can react to various structural shocks.
8 See http://sdw.ecb.europa.eu/browse.do?node=2120781.
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Table 1 VAR system F-tests, 1994:Q1–2008:Q2.
Dependent variable
IRS LSHP LNER INF
IRSt−i 59.155 [0.00] 1.112 [0.34] 0.592 [0.56] 0.294 [0.75] LSHPt−i 3.119 [0.05] 465.67 [0.00] 0.229 [0.79] 0.466 [0.63] LNERt−i 3.553 [0.04] 2.311 [0.11] 2663.1 [0.00] 0.149 [0.86] INFt−i 1.154 [0.32] 4.368 [0.02] 4.972 [0.01] 46.354 [0.00]
Notes: the number of lags (i) included in the VAR is two. The numbers in the table are F-statistic with p-values in the brackets.
3.2. The identification strategy with sign restrictions
In this section, we describe our method in estimating the effects of monetary and asset price shocks by means of sign restrictions, following Uhlig (2005). Identification via sign restrictions is relevant in this context, as our objective is to investigate the effect of shocks due to surprise movements in interest rates, which provide a structural interpretation of inflation shocks. We use the reduced-form of a vector autoregressive (VAR) model of order p with the following standard representation:
Yt = B(L)Yt−1 + ut where the vector Y includes the interest rate spread between long-term and short-term interest rates, the log of the share price for the euro area stock markets, the log of the nominal effective exchange rate and CPI inflation, which are denoted, respectively, as IRS, LSHP, LRER and INF. B(L) is a lag polynomial of order p. The covariance matrix of the vector of reduced-form residuals u is denoted as �. Identification in the structural VAR literature amounts to providing enough restrictions to uniquely solve for the following decomposition of the nxn estimated covariance matrix of the reduced-form VAR residuals ˙.
˙ = E[ut , u′t ] = AE[εt ε′t ]A′ = AA′. This defines a one-to-one mapping from the vector of orthogonal structural shocks ε to the reduced- form residuals u, u = Aε. The jth column of the identifying matrix A, aj, is called an impulse vector, as it maps the innovation to the jth structural shock εj into the contemporaneous, impact responses of all the n variables. With the structural impulse vector aj in hand, the set of all structural impulse responses of the n variables up to the horizon k can then be computed using the estimated coefficient matrix B(L) of the reduced-form VAR.9 Thus the sign restriction approach amounts to simultaneously estimating the coefficients of the reduced-form VAR and the impulse vector.
3.3. Estimation results
We examine the dynamic effects of inflation shocks on share prices, interest rate spreads and NEER. Before we undertake this exercise, we examine the possible linkages between the variables included in our VAR system. We uncover the effects using F-tests as shown in Table 1.
In Table 1, it appears from the inflation equation that none of the variables explain changes in infla- tion, thus making inflation exogenous. As explained above, in Table 1 we only present the preliminary results linking key monetary and financial variables using an unrestricted VAR. The shock analysis will be carried out using a restricted VAR within the sign restriction identification procedure due to Uhlig.
The causation seems to run as follows. It is inflation that causes changes in share prices and nominal exchange rates, both of which in turn explain changes in interest rate spreads. Thus it makes sense to analyse the impact of inflation shocks on these three financial variables namely IRS, LSHP, and LNER. Regardless of the direction of causality, as our objective in the paper is to look at the impact of price stability (or inflation targeting) on financial stability, we examine the impact of an inflation
9 See Dedola and Neri (2007) for more details.
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shock on the three asset prices considered here. This has been supplemented with the ECB policy rate as an alternative proxy for monetary policy shocks to validate the results due to an inflation shock. Note that the VAR is in log levels and the variables are left in non-stationary form because the sign restrictions methodology is robust to the presence of non-stationarity. Although it does not impose any cointegrating long-run relationship between the variables, neither does it preclude the existence of such a relationship.
We apply identifying sign restrictions to the above VAR with four variables, taking account of the empirical approach in Uhlig (2005). The restriction for monetary stability can relate to a negative INF shock, which could increase share prices implying a positive effect on LSHP. We also impose a stylised fact in the monetary policy literature that lower inflation can imply a narrower interest rate spread, suggesting a positive sign on IRS. No restriction, however, is placed on the nominal exchange rate, as we want it to be determined by the model because external factors may influence the exchange rate in an open economy context. Also we do not determine a priori the effect on LSHP, as we wish the impact to be determined by the model.
The responses in Fig. 2 satisfy the sign restrictions for k = 1,. . .,K quarters. The error bands are illustrated as the dotted lines above and below the response line (the thick line), which are composed of the 16th, 84th and median percentiles of the impulse responses for each shock, from a sample of 100 draws from the posterior.
With inflation being restricted not to increase, which is likely to occur as a result of inflation tar- geting, we would expect the spread between long-term and short-term interest rates to narrow and share prices to rise. The nominal exchange rate, which was not restricted, is appreciating marginally due to lower inflation as one would expect. There appears to be a pro-cyclicality between monetary stability and financial stability in the long-run, as shown from the impulse responses in Fig. 2. In the short-run, a decline in inflation has been associated with an increase in share prices, which could be partly due to a decline in the cost of borrowing as reflected in the spread between the two interest rates.
The same result holds when we pre-judge the outcome for the nominal exchange rate not to appre- ciate as observed in Fig. 2. We find the same positive effect on share prices (see Fig. 3) due to a negative inflation shock. Thus we can establish that there is a pro-cyclical relation between monetary stability and stock-market index, even when the shock dies out. This suggests that financial stability may be driven by shocks internally within the financial sector or from the external sources namely macroe- conomic developments or economic policy changes that are likely to have an impact on aggregate
Fig. 2. Impulse responses due to a negative inflation shock (with no restriction on LNER and LSHP).
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Fig. 3. Impulse responses due to a negative inflation shock (with no restrictions on ECB and LSHP).
inflation. That is the principal reason why we examined the effect of negative inflation shocks on asset prices. Theoretically, the effect of the negative inflation shocks can be identified as a supply response story. A supply shock explains the lower level of inflation and hence higher profitability. If it were a demand shock, a drop in inflation should, ceteris paribus, make firms less optimistic and profit projec- tions can fall. Hence, the positive correlation with share prices can be explained by a positive supply shock that lowers inflation and boosts share prices.
However, as the central banks tend to target inflation at a lower level, if inflation were to fall (below target), there would be an attempt to cut the key policy rate, i.e. the lowering of interest rate to get inflation back on target. So we carry out a similar exercise with the ECB policy rate in the VAR (see Fig. 4)
Fig. 4. Impulse responses due to a negative inflation shock (with property price inflation).
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and examine whether the reduction in interest rates boosts already high asset prices and ultimately lead to boom-bust behaviour as suggested in White (2006).
The estimated behaviour of interest rate spreads could also be capturing a positive supply shock in terms of faster total factor productivity growth, leading to long rates rising (general equilibrium effect) and short rates falling, as supply shifts out faster than demand, and short rates fall faster than long rates (Keynesian effect). The easier monetary policy could lower the short rate as well. So, there would be a tendency for the spreads to widen. If the expansionary supply shock did – through the financial accelerator – boost the health of borrowers and lenders over the longer-run, long rates would likely fall more than short rates, which could account the impulse responses for the spread in the long-run. Alternatively, if supply shocks were accompanied by less risk-aversion as suggested by Minsky (1994) and Kindleberger (1996), this channel would also be consistent with the results.
Besides the effect of inflation shocks as a proxy for monetary shocks, we further check the response of stock prices by adding ECB monetary policy rate as an additional variable in the VAR. As inflation targeting may have contributed to financial stability via the interest rate instrument, we have carried out the same analysis by tracking the response of ECB policy rate. Since the central bank reference rate is only available starting from 1999, the Bundesbank discount rate has been used for the earlier period to construct the policy variable. Suppose that inflation has increased due to past-monetary policy. The rise in inflation will prompt a central bank to react by raising interest rates. If the central bank follows a rule close to a Taylor rule, then the rise in the nominal interest rate will result in higher real interest rate, which will induce a decline in aggregate demand and a possible decline in share prices. We find monetary policy response to be expansionary consistent with the earlier negative inflation shock. We find that a negative monetary shock contributes to increasing share prices, while such a monetary easing raises inflation thus bringing in monetary tightening in the long run so as to maintain stability. In other words, with a loose monetary policy response, asset prices react in a negative manner, exhibiting financial stability. There is clear evidence of a pro-cyclical relationship between monetary stability and financial stability even in the long-run.
Further, with the ECB policy rate, the results for share prices suggest a stabilising effect in the sense that 1% negative monetary shock can produce around 2% rise in share prices in the medium term or vice versa. If we consider a feedback mechanism within an open economy Taylor-type policy rule, we can assess the extent to which the ECB policy rate reacts in response to inflation. With a negative shock to inflation, the policy rate declines initially to support stock market and subsequently rises to tame inflation due to a boom in share prices (see Fig. 4). We conclude that consumer price changes seem to be moderately linked to share price fluctuations. And it is monetary stability that drives financial stability (proxied by share prices) suggesting that monetary stability via interest rate adjustment appears to be a pre-condition for financial stability in the euro area.
However, in the context of a low inflation environment with the ECB enjoying a sound anti- inflationary reputation, the resulting investor optimism might lead to excessive risk exposure and thus to asset prices rising far in excess of any reasonable valuation. So besides share price growth found earlier on the back of monetary policy easing, we now bring in residential property price infla- tion (RPP) for the euro area to monitor its response to restrictions imposed earlier. We do not impose any restriction on RPP, but look at its response to a negative shock in inflation as designed earlier (see Fig. 4).
Turmoils in global financial markets do raise concerns about how best to control liquidity conditions. So we augment the VAR by bringing in bank deposit–loan ratio (DLR) as a measure of liquidity. As interest rates ease, it would drive loans and reduce bank DLR, but the reverse does not appear to be case (see Fig. 5). With lower inflation, interest rates decline, but when inflation starts to accelerate driven by demand on the back of stock market boom, interest rates increase, which could reduce loan supply. But the response of DLR showing a declining trend suggests that bank demand deposits also decline in response to a rise in interest rates, showing evidence of a possible switch to long-term savings instruments on the back of higher interest rates.
Besides the case of low inflation and bubbles in house or stock markets, we also consider the scenario of high inflation and low growth (LGDP), and look at the response of stock prices and the composite leading indicator (LIND). Imposing these restrictions of high inflation, low growth and falling house
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Fig. 5. Impulse responses due to a negative inflation shock (with no restriction on LSHP and ECB).
prices, we find that policy makers initially increase interest rates in the short run to stabilise inflation and subsequently reduce rates to boost demand and stabilise output, helping both the equity and housing markets. The responses are presented in Figs. 6 and 7. The results indicate that with monetary stability, the stock market gets a boost, which is reflected in a rise in the composite leading indicator, showing positive business expectations (see Fig. 6). This leading index can also capture movements in
Fig. 6. Impulse responses of a policy rule due to CPI inflation and negative property price shocks (with no restriction on LSHP, ECB, RGDP).
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Fig. 7. Impulse responses of monetary policy and composite leading indicator due to high inflation, low growth, negative property price and stock price shocks. Notes: four restrictions are imposed. Positive inflation shock is imposed along with negative stock and property prices and negative GDP growth.
external market conditions influencing euro area asset prices. Inflation shocks have a strong impact on the asset prices. A negative inflation shock moves the stock market towards a boom; likewise, a positive inflation shock can move the market towards a bust. So one could identify both a decline (increase) in inflation and an increase (decline) in stock and property prices as reflecting a scenario of financial (in)stability. In the sample period under study, we do not see a significant adverse impact coming from external sources. Although our impulse response results indicate stability in the long-run, it is possible that this trend could turn into an asset price bubble. If such a trend develops, how should the ECB respond? Should monetary policy or prudential regulation be used to address such a bubble? This question lies outside the scope of this paper but intuitively the latter approach should be the viable one as monetary policy, with its set of traditional instruments, is ill suited to effectively deal with asset price bubbles. This brings us back to the debate mentioned in the introduction on the need to reach a resolution of the unfinished agenda of financial sector supervision and regulation within the euro area in the sense of empowering a supranational financial regulator.
4. Conclusion
We have investigated the dynamic effects of inflation shocks (a proxy for monetary stability or inflation targeting) on share prices, interest rate spreads and NEER (proxies for financial stability) by means of sign restrictions, following Uhlig (2005). We find that there is pro-cyclicality between these variables in the long-run. The long-run pro-cyclicality implies financial stability, suggesting that the financial system is robust to disturbances in the economy and can channel capital, execute payments and redistribute risk in a satisfactory manner. This long-run result indicates that monetary stability is an important precondition for financial stability. Still financial instability could occur during periods of strong growth in debt and asset prices. With a monetary shock reflected through a shock in inflation, we still find a similar response on the three asset prices considered here. We conclude that long- run price stability or sustained periods of low inflation as reflected in negative inflation shocks have positive stable impact on share prices (the key asset price to monitor for financial stability) in the euro area currency union.
This paper therefore suggests that there is no general trade-off between monetary and financial stability in the long-run. We also brought in residential property prices and a composite leading indi-
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cator as this would seem to be relevant for monetary and financial stability. The results indicate that with monetary stability, the stock market gets a boost, property price inflation rises, and this is in turn reflected in a rise in the composite leading indicator, showing positive business expectations. Inflation targeting or constant inflation might mislead us into pursuing a policy that is actively damaging to financial stability. The pro-cyclical relation holds only in the absence of asset price shocks. If there is a shock to asset prices, which is unrelated to macroeconomic fundamentals, asset prices must be stabilised otherwise a trade-off will exist in the long-run. If a central bank prefers to achieve both, there will be no long-run trade-off.
Appendix A
Zivot–Andrews Unit Root Test.
Notes: for all variables, we allow for breaks in both intercept and trend; minimum t-statistics with break points for the variables IRS, LSHP, LNER, INF, ECB, DLR, LIND and LGDP are, respectively, −4.5063 at 2002:04, −3.3677 at 2001:03, −3.8388 at 1999:01, −2.7719 at 1999:04, −2.6828 at 2003:01, −4.5928 at 1997:03, −4.1373 at 1999:01, and −4.0466 at 1999:01. Critical values are 1% −5.57 and 5% −5.08.
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- Monetary and financial stability in the euro area: Pro-cyclicality versus trade-off
- Introduction
- An analytical setting
- Empirical analysis
- Data
- The identification strategy with sign restrictions
- Estimation results
- Conclusion
- Appendix A
- References
Monetary-policy-and-financial-in-stability-An-integrated-micro-macro-approach_2008_Journal-of-Financial-Stability.pdf
Journal of Financial Stability 4 (2008) 205–231
Available online at www.sciencedirect.com
Monetary policy and financial (in)stability: An integrated micro–macro approach
F. De Graeve a,∗, T. Kick b,c, M. Koetter b,c,d,∗ a Department of Financial Economics, Ghent University, Wilsonplein 5D,
9000 Ghent, Belgium b Deutsche Bundesbank, PO Box 10 06 02, 60006 Frankfurt a.M., Germany
c Institute for the World Economy, Düsternbrooker Weg 120, 24105 Kiel, Germany d University of Groningen, Faculty of Economics, PO Box 800,
9700 AV Groningen, The Netherlands
Received 6 March 2007; received in revised form 30 August 2007; accepted 13 September 2007 Available online 10 October 2007
Abstract
Evidence on central banks’ twin objective, monetary and financial stability, is scarce. We suggest an integrated micro–macro approach with two core virtues. First, we measure financial stability directly at the bank level as the probability of distress. Second, we integrate a microeconomic hazard model for bank distress and a standard macroeconomic model. The advantage of this approach is to incorporate micro information, to allow for non-linearities and to permit general feedback effects between financial distress and the real economy. We base the analysis on German bank and macro data between 1995 and 2004. Our results confirm the existence of a trade-off between monetary and financial stability. An unexpected tightening of monetary policy increases the probability of distress. This effect disappears when neglecting microeffects and non- linearities, underlining their importance. Distress responses are largest for small cooperative banks, weak distress events, and at times when capitalization is low. An important policy implication is that the separation of financial supervision and monetary policy requires close collaboration among members in the European System of Central Banks and national bank supervisors. © 2007 Elsevier B.V. All rights reserved.
JEL classification: E42; E52; E58; G21; G28
Keywords: Financial stability; Stress-tests; Bank distress; Monetary policy
∗ Corresponding authors. Tel.: +31 50 363 3633. E-mail addresses: [email protected] (F. De Graeve), [email protected] (T. Kick),
[email protected] (M. Koetter).
1572-3089/$ – see front matter © 2007 Elsevier B.V. All rights reserved. doi:10.1016/j.jfs.2007.09.003
206 F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231
1. Introduction
This paper investigates interactions between banking sector stability and the real economy. Thereby, we seek to contribute empirical evidence to the ongoing debate among policy makers (ECB, 2006; Deutsche Bundesbank, 2006), academics (Benink and Benston, 2005; Goodhart et al., 2006) and the public (The Economist, 2007), concerning the extent macroeconomic policies and the stability of financial systems depend on each other. Specifically, we investigate how monetary policy affects financial stability and quantify the importance of feedback mechanisms between the real and financial sector.
The twin objective of monetary and financial stability climbed the agenda of central bankers as witnessed by a rampant increase in the number of stability reports published by central banks (Oosterloo et al., 2007). This surging interest in twin stability is presumably owed to a fairly suc- cessful record to control inflation, but increasing concerns regarding financial stability in light of increasing competition and financial integration (Borio, 2006). In addition, if the financial stability of individual banks differs, this is likely to affect the transmission mechanism of monetary policy, too. For example, Kishan and Opiela (2000) demonstrate that loan supply of poorly capitalized banks reacts more sensitively compared to well-capitalized peers.
Empirical evidence on the intricate relation between monetary policy and financial stability is, however, still scarce due to a number of challenges. For starters, the definition of financial stability is surprisingly elusive (Poloz, 2006; Allen and Wood, 2006). Second, central banks’ policies to ensure financial stability vary considerably across countries, thus reflecting both the term’s ambiguity and related problems to measure stability (Oosterloo and de Haan, 2004). Third, a number of scholars emphasize the role of banks for financial stability (De Bandt and Hartmann, 2000; Padoa-Schioppa, 2003; Schinasi and Fell, 2005). But while the number of studies analyzing individual banks’ probabilities of default is fairly abundant,1Jacobson et al. (2005) highlight that only few studies employ microeconomic indicators of financial stability of firms and/or banks to link it to monetary policy and resulting stability responses. Fourth, Goodhart et al. (2004, 2006) emphasize the interdependence of microeconomic agents and macroeconomic performance. Thus, allowing for feedback mechanisms is essential for models that could serve policy makers, for example for stress-testing purposes (ECB, 2006).
We aim to make two core contributions. First, we develop an integrated micro–macro approach that incorporates stability indicators at the bank level into the assessment of macroeconomic shocks and responses. Second, we allow explicitly for feedback mechanisms between both the macroeconomic stance and the microeconomic stability of banks. Contrary to extant research, our approach is agnostic about both the timing and direction of the feedback mechanisms.
To this end we use macroeconomic and individual data for all universal banks operating in Germany. We analyze which different types of distressed events occur more frequently following a monetary policy shock, as well as which banking groups are predominantly affected on the basis of confidential Bundesbank bank data between 1995 and 2004. Thus, we curb the measurement problem of financial stability, which most studies usually face. Financial stability is defined and measured as a bank’s probability of distress according to the supervisor’s definition of problem banks used for supervisory policy.2
1 See, for example Cole and Gunther (1995), Wheelock and Wilson (2000), Estrella et al. (2000), Shumway (2001), Gan (2004), King et al. (2006) and Porath (2006).
2 Note that the probability of bank distress really is a measure of a banks stability mirror image, i.e. fragility. We maintain throughout the terminology financial stability as to conform with the wording of policy makers’ objectives.
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 207
We construct a reduced form micro–macro model which describes the convolution of bank distress probabilities at the micro-level and the macroeconomy. There are a number of reasons to combine the micro and macro perspectives. In a pure macro model, many potentially relevant effects may be obscured due to the loss of information following data aggregation. We find that this effect is substantial. A model based only on financial sector aggregates misleadingly suggests macro–financial feedback to be absent. Moreover, it is not always straightforward to assess how aggregate fluctuations are related to individual bank distress. In turn, with a pure micro approach it is difficult to interpret movements in aggregate variables. Many macro stress- testing exercises incorporate the real economy by specifying some unconditional distribution for aggregate variables. A first drawback of this approach is to preclude financial–macro feedback, also called second-round effects. Second, there is no straightforward economic interpretation of the macro fluctuations, for example in terms of structural shocks. Both are desirable features of models suited for macro stress-testing (Goodhart, 2006; ECB, 2006). By focusing on monetary policy shocks, their effect on and interaction with financial stability, we aim to shed light on the policy implications of macro stress-testing analysis.
The microeconometric part of the model links probabilities of bank distress to both bank- specific and macroeconomic variables. We then combine this model with a macro model describing the dynamics of the main macroeconomic variables, as well as their interaction with the financial sector. Subsequently, we identify monetary policy shocks in the combined micro–macro-system. That is, we identify the reduced form in order to understand the effects of structural shocks. Our approach allows for macro–financial as well as financial–macro feedback dynamics. Moreover, this feedback can be both instantaneous and subject to non-linearities. Model simulations provide insight into the complex interdependence between macro shocks and microeconomic banking stability. This model allows us to measure the interactions between monetary policy and financial regulation more explicitly compared to previous studies on macroeconomic stress. Our study is thus akin to Jacobson et al. (2005), who analyze interactions between the Swedish macroeconomy and the corporate sector using vector autoregressive (VAR) techniques combined with probabilities of distress of individual firms derived from a hazard rate model.
We differ, however, in four important respects. First, we use confidential data provided by the Deutsche Bundesbank to estimate bank rather than corporate firm distress from a panel of bank- specific financial data and distress events. Therefore, we measure financial stability more directly compared to an approach that examines the financial stance by approximation of bank customers stability (Goodhart et al., 2004; Schinasi and Fell, 2005). Second, we disaggregate our measure of distress and according responses to monetary policy shocks along two dimensions: different degrees of distress and different types of banks, respectively. Third, we differ substantially in the way in which we treat the combined micro–macro-system. Our study contributes methodologi- cally by incorporating simultaneity in the macro–financial interactions. We extend the VAR by a data generating process for distressed events, which is estimated on micro bank data. This com- bined system resembles a reduced form panel-VAR. We apply identification techniques to this combined micro–macro-system (i.e. construct a SVAR) to analyze the effect of structural shocks. Importantly, we do so without imposing any a priori restrictions on the direction or the timing of interactions between the macroeconomy and the financial sector, but let the data determine their outcome. Fourth, we analyze the largest economy in Europe, namely Germany. To some extent, our policy implications may thus be of economic significance for the European economy as a whole.
Our main result is that a contraction in monetary policy increases the average probability of distress of banks by 0.44%, which resembles a third of its annual standard deviation. Hence,
208 F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231
the effect is economically significant and indicates a modest trade-off between monetary and financial stability. Second, allowing for feedback effects and non-linearities is crucial. Without modeling individual bank distress probabilities’ reaction to the macroeconomy, a contraction of monetary policy has no significant effect on our measure of financial stability. Consequently, stability studies that neglect the integral role played by microeconomic agents may falsely fail to detect the trade-off between monetary and financial stability. Third, distinguishing different degrees of distress and banking sectors yield heterogeneous responses. Thus, a finer distinction of distress as well as alternative transmission mechanisms at work across banking sectors need to be considered when assessing financial stability. Moreover, the effects of monetary policy on banking sector distress are more severe when the banking sector is poorly capitalized. To the extent that banking distress carries over to banks’ lending behavior, this is in line with the bank lending channel literature. Our results suggest monetary policy transmission is intertwined with the financial health of the banking sector. In sum, the interdependency of the twin objective highlights the necessity for close collaboration between guardians of both price and financial stability.
The remainder of this paper is organized as follows. We present our data in Section 2 and discuss the components of the micro–macro model subsequently in Section 3. Our results in Section 4 are reported for aggregate measures of distress and, in addition, according to banking group and distress level. We conclude in Section 5.
2. The data
The analysis pertains to the German economy and its banking system over the period 1995–2004. We use the distress database of the Bundesbank to model bank distress, which is particularly insightful for our questions of research.3 The German banking sector experienced substantial fluctuations in the occurrence of distressed events. The sample contains more than 1100 events and the aggregate annual frequency of distress fluctuates approximately between 2% and 7% as shown in Table 1.
We observe differences between banking sectors and across distress categories in our sample period. Therefore, we disentangle below responses of probabilities of distress to monetary shocks according to both dimensions and depict next to the aggregate distress frequencies according splits in Table 1, too.
The cross-sectional dispersion in the data is substantial. The different evolution of distress frequencies across banking groups reflects the partition of German banking into three distinct sectors that pursue different business strategies and face accordingly different risks (Hackethal, 2004). For example, the group of small commercial banks exhibits especially during the times of stock market turmoil at the turn of the century exceptionally high frequencies of distressed events. This may reflect a larger dependence on non-interest income and financial market exposure (Koetter et al., 2006). Likewise, especially small cooperative banks experienced distress in the wake of increasingly fierce competition and consolidation pressure (Lang and Welzel, 1999). The pillar-specific pattern of distress suggests that shocks may affect the stability of these banking groups differently, which we investigate below.
Regarding different distress categories, Oshinsky and Olin (2006) point out that banks hardly ever face a dichotomous destiny of either failure or survival. Instead, a number of different
3 See also Porath (2006), Kick and Koetter (2007), and Koetter et al. (2007).
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 209
Table 1 Annual distress frequency according to banking group and distress category
Year All Banking groups Distress categories
Com’cl Sav’s Coop’s I II III IV
1995 1.9% 2.2% 0.3% 2.3% 0.1% 0.4% 0.8% 0.6% 1996 2.5% 4.9% 0.8% 2.8% 0.1% 0.4% 1.2% 0.7% 1997 3.4% 6.3% 0.9% 4.0% 0.1% 0.7% 0.9% 1.7% 1998 4.7% 7.5% 2.1% 5.3% 0.1% 1.4% 1.3% 1.9% 1999 5.6% 4.4% 0.7% 7.2% 0.2% 2.4% 0.9% 2.1% 2000 5.0% 5.0% 1.6% 6.1% 0.1% 2.2% 1.0% 1.7% 2001 6.9% 9.2% 2.2% 8.3% 0.8% 3.1% 1.1% 1.9% 2002 7.0% 4.4% 3.4% 8.7% 1.2% 3.3% 0.9% 1.6% 2003 6.6% 4.7% 1.8% 8.8% 0.8% 3.4% 1.1% 1.3% 2004 4.1% 0.8% 1.1% 5.8% 0.5% 2.5% 0.8% 0.3% Observations 26012 1509 5569 18736 24967 25325 25131 25226
shades of distress can occur to a bank. Based on detailed data on approximately 60 different possible events collected by the Bundesbank, we distinguish four increasingly severe classes of distress labeled I through IV in Table 1.4 The first group of weakest events includes three inci- dents. First, compulsory notifications by banks about events that may jeopardize the existence of the bank as a going concern according to §29(3) of the German Banking act (“KWG”). Sec- ond, a notification by banks of losses amounting to 25% of liable capital according to §24(1)5 KWG. Third, weak measures like letters of warning. The second distress category captures measures taken by the Federal Financial Supervisory Authority (“B aFin”) representing offi- cial warnings, admonishment hearings, disapproval, warnings to the CEO, and serious letters. None of these measures imply an active intrusion into the ongoing operations of the bank. In turn, category III represents corrective actions against the bank such as orders to restructure operations, restrictions to lending, deposit taking, equity withdrawal or profit distribution or the dismissal of management. The fourth (and worst) distress category comprises takeovers classified by the Bundesbank as restructuring mergers and enforced closures of banks initi- ated by the BaFin, which are extremely rare. The pattern depicted in Table 1 highlights that in particular weaker distress events occurred more often in recent years. Potentially, weaker incidents are more likely during monetary contraction but structural distress, such as market exit through mergers, may not be affected by such temporary phenomena but depend on funda- mental deficiencies of the bank. We therefore test below if responses do differ across distress categories.
Often, macro stress-tests focus on credit risk alone. According to Aspachs et al. (2007), the probability of distress is a much more appealing statistic to measure financial (in)stability. The- oretically, it provides a sufficient statistic for the relation between individual banks’ probability of distress, their exposure to various measures of risk, and the macroeconomic stance. Thus, the probability of distress provides a more exhaustive picture of stress borne by the banking system and considers, in contrast to other stability studies, all types of risk.
4 Next to the annual distress database of the Bundesbank, we also use three subset databases with exact dates (“measures”, “incidents” and “mergers”) to construct below a quarterly series of the distress indicator for reasons explained in Section 3.2.
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3. Methodology and auxiliary results
We first introduce our approach to measure financial stability at the bank level with a hazard rate model. The particular model deployed is a logit model that relates bank-specific probabilities of distress to bank-specific as well as macroeconomic conditions. Subsequently, we discuss our specification of the reduced form macro model. The macro model is a VAR for key macroeconomic aggregates. Up to this point, our methodology is very similar to the one of Jacobson et al. (2005). The latter identify a monetary policy shock in the macro model and verify its impact on the micro financial model. The financial impact then may affect macro developments in a subsequent period. In a third subsection we lay out the way we combine the reduced form micro and macro models, which is different from that in Jacobson et al. (2005). In particular, we combine the reduced form micro and macro models in one integrated system. We then identify shocks in the combined micro–macro-system. This has two virtues relative to the approach of Jacobson et al. (2005). First, the identification of the shock takes into account the financial effect, as well as possible non-linearities. Second, we do not need to make assumptions about the timing of real–financial interactions. We regard this as an important feature of models analyzing stability in the financial sector. Specifically, since a broad consensus on theoretical models of financial stability does not exist yet, somewhat contrary to monetary policy models, imposing restrictions on financial sector interactions with the real economy is harder to defend.
3.1. A microeconomic measure of financial stability
The microeconomic component of our integrated model captures the driving forces of the probability of distress (PD) among banks. In particular, we estimate the conditional probability of distress with a logit model:
PDit = eβXit−1+πZt−1
1 + eβXit−1+πZt−1 (1)
Here, PDit denotes the probability that bank i will face distress in year t. It is estimated from a set of covariates Xit−1 observed for bank i in period t − 1 and, additionally, a set of macroeconomic covariates Zt−1, where β and π are parameters to estimate. The micro model transforms a set of bank-specific and macroeconomic covariates observed in year t − 1 into bank-specific PD’s with an appropriate link function, in our case a logit link function.5
Since the number of bank-specific covariates to include in X is possibly immense, we follow the procedure suggested in Hosmer and Lemshow (2000) and pre-select an economically meaningful long list of around 150 covariates. We orient ourselves at the rating practices followed by super- visory authorities, which use the so-called CAMEL taxonomy (King et al., 2006).6 Within each category we conduct univariate tests to identify a shortlist of covariates that maximize explana- tory power.7 Ultimately, we select a final vector of seven bank-specific and three macroeconomic variables by means of stepwise regression. Descriptive statistics according to banking group and distress category are provided in Table A.1 in the Appendix A.
5 The link function transforms the variables’ effects into probabilities. The particular choice for a logit essentially leaves our results unaffected (see also Porath, 2006). Based on standard lag selection criteria, we use 1 year lags for all variables.
6 CAMEL: capitalization, asset quality, management, earnings, liquidity. 7 For a more detailed description of model selection for Bundesbank data see Porath (2006), Koetter et al. (2007) and
Kick and Koetter (2007).
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 211
More importantly in the light of our study is the inclusion of three macroeconomic covariates (Zt = (Y, P, R)t′ , denoting respectively output growth, inflation and the interest rate) as an addi- tional category of its own. These are included to establish the link with the macroeconomic VAR model. Moreover, the evolution of both bank-specific and macroeconomic covariates over time, depicted in Fig. A.1 in the Appendix A, shows that no individual model component alone appears to perfectly coincide with observed distress events.8 This corroborates Porath’s (2006) point that macroeconomic and bank-specific covariates are jointly relevant to predict bank distress.
Consider first the hazard rate model in Eq. (1) for the sample pooled across banking groups and distress categories depicted in Table A.2. This hazard rate model exhibits a good fit as witnessed by a pseudo-R2 of approximately 11%. This is on the low side compared to Jacobson et al. (2005), who report aggregated (Laitila) pseudo- R2s calculated for the full sample between 16% and 39%.9 While these are in line with results reported in other corporate failure studies, our goodness of fit measure is fairly well in line with international bank failure studies (see for example Ramı́rez, 2003 reporting R2 between 6% and 13%) and previous studies on German bank distress.10 Hence, the difference of these measures may merely reflect the different hazard rate models, namely corporate versus bank distress, respectively.
Finally, Wooldridge (2002) and Hosmer and Lemshow (2000) caution not to over-emphasize pseudo- R2s to assess the adequacy of limited dependent variable models. In fact, the ability of hazard rate models to correctly discern events from non-events is crucial. The classification of predicted events depends on the probability cutoff level beyond which an observation is assigned to either one of these classes. In contrast to studies reporting types I and II classification errors (Kolari et al., 2002), we follow Hosmer and Lemshow (2000) and evaluate the discriminatory power of the model over the range of alternative cutoff levels between zero and one by means of the area under the Receiver Operating Characteristics (ROCs) curve. The area under the ROCs curve (AUR) measures the percentage of correctly classified events (sensitivity) versus one minus the percentage of correctly classified non-events (specificity). It is thus more general and informative compared to types I and II errors or R2.
According to Hosmer and Lemshow (2000), the reported AUR values of around 77% indicate a good ability of this model to discriminate successfully between distressed and non-distressed events. Even though our prime interest is not in individual parameter estimates, it is comforting that virtually all coefficients are significantly different from zero and exhibit signs and magnitudes in line with other bank failure studies. We also depict parameter estimates for group-specific logit models in the right-hand panels of Table A.2. Like the aggregate model, each specification exhibits fairly high AUR values. Since our prime focus in this paper is to assess the effects of monetary policy on financial stability, we refrain from further inference and turn next to the macroeconomic component of the model and its relation to bank stability.
Table 2 sheds light on the importance of incorporating macroeconomic variables in the micro model. The table compares two measures of fit across our baseline model with and without macro covariates.11
Including macro variables helps the micro model in two important ways. First, consider the aggregate root mean-squared errors (A-RMSE). This measure reflects the success of both models
8 We discuss the respective contribution to the discriminatory power of the micro model in more detail below. 9 We check if this could be attributed to our choice of 1 year lags for all covariates in the bank hazard model, i.e. including
macro covariates, which differs from the contemporaneous specification of macro terms in Jacobson et al. (2005). This turns out to be not the case since R2 declines to 10.6% in the latter specification. 10 For example, Koetter et al. (2007) and Kick and Koetter (2007) report R2 between 11% and 13%, respectively. 11 Parameter estimates without macro variables are in Table A.3 in the Appendix A.
212 F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231
Table 2 The contribution of macro covariates to discern bank-specific distress
All Banking groups Distress category
Com’cl Sav’s Coop’s I II III IV
A-RMSE Micro only 0.015 0.024 0.008 0.017 0.003 0.010 0.002 0.006 Micro and macro 0.011 0.016 0.007 0.013 0.002 0.008 0.002 0.003 Reduction (%) 28.45 36.17 12.79 21.67 43.12 14.41 27.92 40.44
AUR Micro only 0.77 0.62 0.84 0.77 0.83 0.72 0.85 0.78 Micro and macro 0.77 0.66 0.84 0.78 0.84 0.74 0.85 0.80 Gain (%) 1.04 6.65 0.68 0.95 1.09 2.30 0.00 1.62
Notes: A-RMSE: aggregate root mean squared error; AUR: area under the Receiver Operating Characteristics curve.
in capturing the aggregate rate of distress over time. Macro variables reduce projection errors by at least 14% and up to 40%. Second, Table 2 also contains a measure that reflects the cross-sectional fit of the model with and without macro variables: the AUR. Here, we also see that incorporating macro covariates improves the cross-sectional success of the model. In particular, we observe a gain in AUR of up to 6% for commercial banks.
This model comparison exercise implies, first, that the macro variables improve the estimation of the marginal effects of the hazard model. Importantly, the identification of macro effects requires both the micro (cross-section) and macro (time series) dimension (Porath, 2006). This reduces potential concerns with respect to the fairly short time series dimension of the data. Second, the success of the model in reproducing the aggregate distress rate is intimately tied to the inclusion of macroeconomic information. This result is in line with Jacobson et al. (2005), who also highlight the crucial importance to include macro variables when fitting a default model for Swedish firms to capture aggregate movements.
3.2. The macroeconomic model
The macro block of the model is a standard vector autoregressive model (VAR), describing the convolution of the most important macroeconomic aggregates. We incorporate financial–macro feedback by allowing these macro variables to depend on our measure of financial stability. We favor a VAR approach for a number of reasons. First, reduced form VARs typically perform very well in capturing the data generating process of macro-aggregates, and the German data are no exception. Second, the interactions between financial stability and the real economy have not been rigorously identified theoretically. Goodhart et al. (2006) is a very important contribution toward this goal. However, a consensus view on these interactions has yet to emerge as pointed out by, for instance, the ECB (2005). The contemporaneous and lagged intricate relation between the real economy and the banking sector is hardly to be measured with a theory-based approach without either heroic assumptions or sole focus on single market segments, such as for example aggregate lending. We therefore aim to impose as little a priori theorizing as possible. VARs render the most flexible way to do so.12
12 Though complete structural models also have a VAR representation, they comprise many more cross-equation restric- tions. Precisely because of the lack of consensus on such restrictions within a framework for financial stability, we refrain from imposing them.
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 213
Specifically, the macroeconomic model consists of a quarterly VAR for GDP growth (Y), inflation (P) and the interest rate (R). Any macro analysis of monetary policy issues typically includes (at least) these three variables. Here, in view of the interest in financial stability, the probability of bank distress (measured by the frequency of distressed events) is incorporated as an additional explanatory variable. The reduced form macro model thus has the following structure13:
Zt =
⎡ ⎢⎣
Y
P
R
⎤ ⎥⎦
t
= ΠMM ⎡ ⎢⎣
Y
P
R
⎤ ⎥⎦
t−1
+ ΠMFPDt−1 + ut (2)
where the Π matrices capture the reduced form feedback coefficients from macro to macro (ΠMM, dimension 3 × 3) and from the financial sector to the macro side (ΠMF, 3 × 1), respectively.
3.3. The integrated micro–macro model
3.3.1. The reduced form After describing both the micro and macro blocks of the model, we now focus on the combined
model. Note that the model in Eq. (2) is a plain VAR augmented with a measure of financial stability as an additional explanatory variable. Put differently, this model does not incorporate any feedback mechanism from macroeconomic conditions to the financial sector. Therefore, we expand the macro system with one equation, namely the data generating process for the aggregate probability of distressed events originating from the micro model.⎡
⎢⎢⎢⎣ Y
P
R
PD
⎤ ⎥⎥⎥⎦
t
= (
ΠMM
ΠFM
)⎡⎢⎣ Y
P
R
⎤ ⎥⎦
t−1
+ (
ΠMF
ΠFF
) PDt−1 + εt (3)
Put differently, the fourth equation of the combined model describes the relation between the probability of distress and the macro variables. The bank-specific variables are considered as exogenous for the combined model.14 They do, however, retain an important role in the model. That is, the coefficients ΠFM are the marginal effects of the macro variables on the financial sector, i.c. the frequency of distressed events. These marginal effects depend on the level of each of the variables in the micro model. For example, the elasticity of distress with respect to output depends, among other CAMEL covariates, on bank capitalization. The same holds for all variables in the system. Moreover, as output changes, all the marginal effects dynamically change along. Thus, the model allows for the possibility of state-dependent coefficients, such as dependence on the balance sheet of the financial sector, an experiment we conduct in Section 4.6.
Considering the micro component in the integrated VAR improves the fit considerably as shown by the improvement of aggregate RMSE in Table 3. Note that, in contrast to the comparison of hazard rate models before, we compare here the integrated model relative to a plain VAR merely augmented with the frequency of distress as an additional endogenous variable. The improvement
13 For expositional purposes, we write the system as a first order VAR. The implementation of the approach, however, does not constrain lag length. 14 Therefore, they do not appear as separate variables in the combined dynamic system. We aim to endogenize banks’
balance sheets in future research.
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Table 3 The contribution of micro to the integrated VAR
A-RMSE All Banking groups Distress category
Com’cl Sav’s Coop’s I II III IV
Macro only (VAR) 0.016 0.031 0.018 0.018 0.009 0.010 0.005 0.005 Micro and macro 0.011 0.016 0.007 0.013 0.002 0.008 0.002 0.003 Reduction (%) 31.00 48.75 61.05 26.70 81.43 18.59 68.38 28.08
Notes: A-RMSE: aggregate root mean-squared error.
of 31% underpins that the micro model also improves the description of the aggregate distress rate relative to a specification including macro only, i.e. a plain VAR. This substantial gain highlights the importance of accounting for both micro information and non-linearities, which help to capture the dynamics of the aggregate distress rate.
3.3.2. The structural form Note the following about the structure of the combined micro–macro model (3). First, the model
is a reduced form. It combines two lower layer reduced form models, in which no contemporaneous relations among the variables exist. The absence of such interactions is what crucially distinguishes this model from a structural model. Second, the model fits into a panel-VAR type framework. That is, all variables are explained in terms of lags of themselves and all other variables in the system. In fact, the model is a mixed panel-VAR since the macro variables are measured in the aggregate, while the probability of distress is measured at the cross-sectional bank level.
Acknowledging this structure of the combined model, one can transform this reduced form into a structural form using standard identification techniques. Similar to transforming a reduced form VAR to a structural one (SVAR), one can identify the above combined micro–macro-system. A complete structural model, as in Eq. (4) below, describes the entire set of relations (both contemporaneous (A, 4 × 4) and lagged (B, 4 × 4)) between all variables in the system, and thus the response to each possible structural shock st (4 × 1).
A
⎡ ⎢⎢⎢⎣
Y
P
R
PD
⎤ ⎥⎥⎥⎦
t
= B
⎡ ⎢⎢⎢⎣
Y
P
R
PD
⎤ ⎥⎥⎥⎦
t−1
+ st (4)
We partially identify the combined micro–macro-system. In particular, we identify a monetary policy shock. Intuitively, we look for all possible structural models that satisfy, first, the reduced form combined micro–macro model in Eq. (3) and, second, what we “know” happens after a monetary policy shock. Regarding the latter, we define a policy shock as one which initially has a positive effect on the interest rate, while neither increasing growth nor inflation (R > 0, Y ≤ 0, P ≤ 0). This is a common set of restrictions in the macro literature (Peersman, 2005).
We identify monetary policy shocks using sign restrictions. Sign restrictions are used rather than a recursive identification scheme. There are, within the current setup, a number of reasons for doing so. First, this approach naturally extends into considering other types of structural shocks, such as demand and supply shocks (Peersman, 2005). Though beyond the scope of the current paper, identifying other shocks may be of particular interest in stress-testing exercises. Second, note that the restrictions we impose (R rises, Y and P do not fall) nest the recursive (or
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 215
Choleski) response. In a recursive identification scheme the imposed instantaneous response is that R rises, while Y = 0 and P = 0. In that sense, our identification is more general, relative to that of Jacobson et al. (2005). The approach differs in an important additional respect. The model of Jacobson et al. (2005) does not allow for any contemporaneous feedback from the financial side to the real economy. Our model can encompass such effects. The absence of a rigorous, widely accepted theory of financial stability makes it clear that such feedback effects should not be precluded a priori. The advantage of sign restrictions is that we can remain fully agnostic about the distress response to a monetary policy shock. A final virtue of the use of sign restrictions is related to the periodicity of the data. Our baseline model is annual in frequency. Many of the more traditional exclusion restrictions are only reasonable for higher frequencies.
3.4. Periodicity of distress
The data used to estimate the micro and macro models presented above have different fre- quencies. While the micro model is based on annual data, VARs are typically estimated on higher frequency data, quarterly in our case. The different periodicity is dealt with as follows. We estimate the reduced forms of the micro model (1) and the macro (2) model separately. Prior to combining the two models, we convert the VAR to its annual form. This makes the frequency equal for both models, enabling their combination. An alternative approach could combine the models at the quarterly frequency. However, because such approaches are very demanding in terms of the time series dimension of the data, we combine the models at the lower, annual frequency.
Quarterly estimation of the macrocomponent of the model requires us to transform the annual distress measure to a quarterly series by employing an according indicator. The latter is constructed from three sub-databases of the annual distress catalogue of the Bundesbank, which indicate specific dates for individual measures (“Maßnahmen”), incidents (“Vorkomnisse”) and (distressed) mergers. While these subsets cover around 75% of all events specified in Eq. (1), the quarterly distress indicator is thus an approximation.15 Akin to Hoggarth et al. (2005), we use the former as a weighting scheme to distribute the annual distress series to quarters. Because there remains some periodicity,16 the quarterly series is smoothed via a four quarter moving average in a second step. The annual and quarterly raw data as well as the de-seasoned weighted annual series are shown in Fig. 1.
The series follow similar trends over time and thus provide only limited reason for concern regarding significant changes of their respective informational content. But naturally, any approach to distribute the annual distress series across quarters is inherently heuristic.17 The first reason for the suitability of this approach is in our case that the quarterly series used to construct the weighting scheme is closely related to the definition of distress according to regulatory authorities. Instead of using some correlated variable without a necessarily meaningful economic relation, the data we exploit forms the major share of raw data to generate the distress database of the Bundesbank. Hence, the information contained in these data should not contaminate our estimates of probabilities of distress. It might, however, add measurement error regarding the exact timing of events.
15 For example, category III events contain capital injections, which could not be included in the quarterly series since data are only available annually. 16 For instance, a number of events are only recorded at the end of the year. 17 Different periodicity in macroeconomic studies is a frequently encountered problem. See Schumacher and Breitung
(2006) for a discussion and a suggested remedy.
216 F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231
Fig. 1. Quarterly and annual distress frequencies.
As a robustness check, we also execute an alternative approach to tackling the frequency mismatch and estimate the integrated model on a quarterly basis. Aware of the uncertainty about the exact timing of the distressed events, we estimate (1) where the left-hand side information now originates from the raw quarterly distress data. For the right-hand side variables, the balance sheet variables are assumed constant within a given year while the true quarterly macro-aggregates are incorporated. A similar approach is used in Jacobson et al. (2005).
According parameter estimates of the micro model are depicted in Table A.4 in the Appendix A. Additional measurement error in the quarterly model appears to be present as shown by a lower R2 of around 8.2%. However, the discriminatory power deteriorates only slightly from an AUR value of 77 to 76. This indicates that the periodicity transformation does not change the informational content of the regressors for the PD measure substantially. Importantly, and in line with Jacobson et al. (2005), parameters of bank-specific covariates are hardly affected in terms of the direction of effects, their significance, and magnitude. This is comforting given the dominant contribution of bank-specific rather than macroeconomic effects in the hazard model. Macro parameters mimic this result with the exception of the estimate of the coefficient of the interest rate. Its change, however, does not necessarily imply that according responses simulated for the monetary shock are spurious. This, in turn, depends ultimately on the resulting responses of financial stability to monetary shocks, which we discuss in Section 4.3 below.
4. Results
We first analyze the effects of monetary policy shocks on financial distress in the combined micro–macro-system to indicate the average historical interrelation between monetary policy stance and the degree of financial stability. Subsequently, we present evidence on the importance of the micro–macro interdependence in this model, the robustness of results relative to an alternative
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 217
Fig. 2. Financial stability response to monetary shock with feedback.
periodicity treatment, as well as detailed evidence according to different banking groups, types of distress, and capitalization states of the banking industry.
4.1. The aggregate response
Fig. 2 plots the median impulse response functions and corresponding confidence intervals of all variables in the system to a monetary policy shock. The impulse responses are annual.18
Therefore, a one standard deviation increase of the interest rate of around 0.1%, is compatible with, e.g., a two quarter increase of 20 basis points, or a one quarter increase of 40 basis points. On the macro side, this reduces GDP growth and inflation with 0.2% and 0.15%, respectively, during the first year. These magnitudes are comparable to other monetary VARs.19
While the instantaneous response of the probability of distress is insignificant, our results indicate a significant deterioration of financial stability in response to restrictive monetary policy after 1 year. Quantitatively the period 1 median response is 0.44%. Though this may seem small at first sight, it amounts to about one third of the annual standard deviation of the distress frequency. A variance decomposition depicted in Table 3 confirms the quantitative significance of this response. Up to about one third of the variance of distress can be accounted for by monetary policy shocks. At the same time, the portion of variance explained of the macro variables is in line with extant macroeconomic research. Monetary shocks are not one of the main drivers of real fluctuations. On average, they explain about 10% of the forecast error variance of growth and inflation.
18 Recall that the macro model is estimated quarterly but rewritten in annual form, in order to align its frequency with that of the micro data. 19 Smets and Wouters (1999) report for Germany virtually identical point estimates.
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Table 4 Variance decomposition of the integrated model
Variable Bounds
Lower Upper
Y (change in real GDP) 2% 19% P (inflation) 2% 17% R (interest rate (3 months)) 1% 8% D (distress frequency) 5% 35%
The significant increase in the distress frequency is important since it shows that monetary policy affects the stability of the financial sector. In particular, it suggests that curbing inflation comes at the cost of lowering financial stability. Hence, we find evidence in support of the existence of a trade-off between the two main goals of central banks.
Given the institutional dichotomy between national supervisory authorities, usually central banks and/or other government agencies (Barth et al., 2001), and the European Central Bank’s mandate to conduct monetary policy in the European Monetary Union, the presence of a trade- off between the two goals underlines the importance of intensive supra-national coordination between policy makers. Hence, the need for a harmonized definition of financial stability paired with concerted efforts by members of the European System of Central Banks forwarded by, for example, Allen and Wood (2006) or Borio (2006), are corroborated by our findings.
While qualitatively in line with Jacobson et al. (2005), our result differs in terms of timing since it contradicts the immediate financial stability response reported for the Swedish economy. A potential explanation could relate to the fact that they measure financial stability as corporate,s’ probabilities of default. Thus, the result for the German sample might reflect that corporate distress relates to bank distress with some lag. An economic rational is that especially banks possess expertise to form expectations and insure against changes in monetary policy while corporates do not (to that degree of sophistication). Hence, a monetary contraction might have no significant instantaneous impact on bank PDs. This seems also reasonable from a more technical angle since the discriminating power of the hazard rate model is primarily determined by the micro variation across banks rather than macroeconomic effects. However, since the integrated model allows for continuous interaction between the real and the financial sector, bank PDs may respond later when solvency pressure on corporates is passed on to banks balance sheets, for example in terms of more non-performing loans and deteriorating profitability.
Alternatively, our approach to estimate an annual model may simply camouflage some of the intra-annual dynamics. The lack of a fully covered quarterly bank distress series and, more importantly, according bank-specific covariates prohibits in our view an ultimate answer to this question. However, we consider below the qualitative implications for the aggregate response based on the quarterly PD estimations assuming constant bank-specific covariates during the year and a quarterly VAR. Beforehand, we consider the importance to allow explicitly for the micro–macro interdependence.
4.2. The importance of accounting for micro and non-linearity aspects
Importantly, the identified trade-off between monetary and financial stability does not emerge in a traditional VAR. The absence of a significant change in financial stability is shown in Fig. 3. The impulse responses shown are those of a plain VAR on (Y, P, R, PD). In such an approach, the
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Fig. 3. Financial stability response in a plain VAR.
aggregate frequency of distress is solely explained on the basis of macro data, without accounting for microeffects as is done in the integrated model.
The figure shows that, based on a standard VAR which does neither account for micro data nor non-linearities, we find no effect of the policy shock on the frequency of distress. The deceptive absence of a response of financial stability is in line with Jacobson et al. (2005), who also report no impact of a policy shock on firm defaults when ignoring the micro side of the data. Our result underlines the importance to allow for possible repercussions of monetary policy at the bank-level, as stated in many central banks’ wishlists for macro stress-testing analyses (ECB, 2006).
The importance of the microeffects is not only intuitively appealing, but also economically reasonable. While bank PDs may depend to some extent on macroeconomic conditions, too, most of the historical distress incidents are explained by bank-specific factors such as capitalization, profitability and asset quality. Direct effects of temporary and moderate changes in monetary policy are thus unlikely to affect aggregate bank PDs significantly. However, a monetary con- traction’s well-documented depression of output may very well affect some banks’ financial accounts through its effect on their borrowers and financial markets in subsequent feedback effects. In an environment of stable inflation and growth, Borio (2006) cautions that a process can unfold where demand side pressure paired with a misperception of risk and wealth as well as looser credit constraints foster the build-up of financial imbalances of firms and households. Excessive demand side pressure may then entail failure of financial institutions to build up suf- ficient buffers but to rely, for example, on financial markets to hedge risks (Driffill et al., 2006). These may shield banks from instantaneous effects in response to efforts by central banks to control inflation. But their customers’ imbalances will dynamically lead to deteriorating deter-
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Fig. 4. Stability responses from a quarterly integrated model and a plain VAR.
minants of bank distress in subsequent periods. The crucial importance of such dynamic effects (and potential non-linearities) has also been raised by Poloz (2006), who cautions that failure to account for the former, as in the majority of twin stability studies, may render inference futile.
4.3. Is it the data?
In Section 3.4 we considered to what extent the microcomponent of the model is affected by the periodicity transformation of the bank failure series. Here, we test whether the identified trade-off between monetary and financial stability is driven by the transformation of our key variable to measure financial fragility: the PD. Following the approach laid out in Section 3 we use the quarterly hazard rate model depicted in table A.4 in the Appendix A in conjunction with a quarterly VAR to simulate responses for a monetary shock. The according results in Fig. 4 demonstrate that the presence of a trade-off between monetary and financial stability persists.
The magnitude of PD response in an integrated model is strikingly similar to that reported for the annual model depicted in Fig. 2. Note that the response of distress is obscured in a plain quarterly VAR. This result is identical to the one obtained from the annual model and therefore corroborates two of our most important conclusions. First, the existence of a trade-off between monetary and financial stability and, second, the importance to consider the intricate relation between the micro and macrocomponent of the model explicitly. But we do find differences in terms of dynamics regarding the integrated model. In the quarterly model, responses show a significant instantaneous effect, which lasts for one period. The fact that the timing of the response is different is not too surprising, given the substantial uncertainty surrounding the exact (quarterly) timing of events in the raw data. In fact, it underpins our earlier cautioning with regards to the precise timing of events predicted by the model for this sample. However, it also demonstrates that the absence of
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Fig. 5. Financial stability responses per banking group.
instantaneous financial stability responses to a tighter monetary stance documented by Jacobson et al. (2005) is not merely the result from differences in the methodological set-up pursued here.20
Given the inherent uncertainty regarding the exact timing of distressed events paired with the lack of quarterly bank data, we caution to draw firmer inference on the exact dynamics of responses. Instead, we limit ourselves to conclude that both models consistently provide evidence in favor of a trade-off between the twin objective of central banks. Since the exact dynamics are subject to care, we focus next on differences in responses across banking groups, types of distress, and states of capitalization in the industry.
4.4. Dissecting the evidence: types of banks
Banks differ considerably in Germany’s so-called three-pillar system in terms of both fund- ing structure and investment portfolios (Koetter et al., 2006). These differences across banking groups also have implications for the transmission of monetary policy since bank lending reacts differently across these pillars as shown, for example, by Kakes and Sturm (2002) and Eickmeier et al. (2006). Financial stability responses are therefore likely to differ across bank- ing sectors, too, and accordingly we also disaggregate our results. In Fig. 5, we present the impulse response functions of three types of local banks: commercial, savings and cooperative banks.21
Most of the differences of banking group responses rest to a lesser extent with the dynamics, but rather in the quantitative reactions. The response of savings banks is significant, though relatively
20 For example, a lagged relation between macroeconomic conditions and bank distress in the microcomponent of the integrated model. 21 The focus on local banks originates in the lack of data on distressed events for the large nationwide banks. In a sense,
this lack of data in itself presents the result for these large banks: they faced no distressed events during the observation period.
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Fig. 6. Financial stability responses across types of distress.
small at 0.1% compared to the aggregate response. The median response of the commercial banks is substantially higher. The largest response is the increase in the distress probability of cooperative banks. Commercial and cooperative banks react, respectively, about three and more than four times as much as savings banks.
One possible explanation for the fairly low response of local savings banks is related to the two-tier structure of this banking sector. Funding-wise, local savings banks rely to a con- siderable extent on the respective central savings bank (“Landesbanken”) they are associated with. The latter, in turn, raise funds in international bond markets. This two layer structure may shield local savings from interest rate changes due to tighter monetary policy if central savings do not pass through interest rate changes to the full extent. Furthermore, the most impor- tant funding source of local savings banks are customer deposits, of which many are in fact savings deposits of households serving as a storage of wealth. These appear to be rather inelas- tic with respect to a decline in aggregate income and raising opportunity cost due to a hike in nominal interest rates. Another reasoning relates to the public ownership of these banks. Explicit state guarantees might have partially insulated this banking group’s probabilities of distress to a large extent from interest rate movements if the former implied funding advan- tages during monetary tightening relative to competitors without such guarantees (Brunner et al., 2004).
While cooperative banks exhibit a similar two-tier structure and also rely extensively on customer deposits as a source of funding, their typical customer portfolio differs consider- ably from that of an average savings bank. Specifically, these banks are very small and serve historically agricultural and small trade SMEs in rural areas (Hackethal, 2004). The mutual ownership structure of these banks implies that most customers are also members and thus own-
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 223
ers of the bank (Altunbas et al., 2001). Consequently, changing interest rates maybe difficult to translate into higher yields on new credits to these member-customers, who however may very well press for more favorable rewards on their deposits. Likewise, the dispersed owner- ship of these mutual banks could imply poor incentives to monitor managers, who in turn have lower incentives to insulate the bank against excessive risks. Finally, these smallest banks in Germany’s industry may employ relatively unsophisticated risk management systems. Then, a change in the monetary stance may affect funding cost much more directly compared to larger banks if asset-liability management practices are conducted without the adequate use of financial instruments.
These two-tier structures contrast with that of local commercial banks, which have no head institution. This may imply substantial costs to evaluate risks as well as in constructing hedged positions. However, the lower response of local commercials compared to cooperatives could be due to the different ownership structure. In contrast to the latter, local commercial banks have shareholders similar to firms in the corporate sector. These may impose a sufficient degree of discipline on the bank’s management. The relative resilience of commercial banks is consistent with shareholders whose quest for profit maximization requires them to at least partially hedge various risks. By contrast, the relatively high exposure to risk of cooperative banks is compatible with a group of shareholders for whom monitoring is less evident.
4.5. Dissecting the evidence: types of distress
We also acknowledge the argument raised by Oshinsky and Olin (2006) that banks hardly ever face only two options: to fail or not to fail. In contrast, the nature of events that we observe describes diverse degrees of distress. We investigate how the four increasingly severe subcate- gories of financial strain defined in Section 2 are affected by policy shocks. The categories we consider are labeled as “automatic signals” (category I), “warnings by the financial authority” (category II), “measures by the financial authority” (category III) and “defaults and acquisi- tions” (category IV) in Fig. 6. We plot how each of these categories respond to monetary policy shocks.
The figure shows that predominantly events of the relatively weak category II “warnings by the financial authority” respond significantly. This response closely resembles the aggregate response of Fig. 2. Thus, following a monetary restriction, about 0.40% of banks run into difficulties, causing an official warning. 80% of the events within this category comprise admonishment hearings, disapproval, serious letters and warnings to the CEO.
The response of the automatic signals also significant, though substantially smaller. However, its response may underestimate the actual impact, because in the case of simultaneous events, only the most severe event is registered. The most severe categories III “measures by the finan- cial authority” and IV “defaults and acquisitions” show no systematic reaction to the stance of monetary policy.22
These results suggest two implications. First, monetary policy shocks alone do not cause supervisors to prohibit certain bank activities, or worse, close the bank. This is not too surprising: the more severe corrective actions seem to be more closely related to structural deficiencies of a bank rather than an unexpected change in the monetary stance. Second, and related, a number
22 Note that since these categories are the most severe, and the severest is always recorded, their non-response is not potentially underestimated.
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Fig. 7. Financial stability responses for different capitalization states.
of banks appear to have entered business activities that brought the bank to the verge of early indications of distress. While monetary shocks are unlikely to take a bank out of business due to outright failure, an increasingly competitive environment could have induced managers to exhaust the risk-taking capacities of their business just before catching regulatory attention. A monetary shock could then induce a fairly large portion of institutes to tumble over the rim and be put on the watchlist of financial stability guardians.
4.6. Banking sector capitalization and the resilience to shocks
It is reasonable to suspect that the relation between monetary policy and financial stabil- ity is subjected to initial conditions. Specifically, we analyze wether the effects of monetary policy shocks differ depending on the degree of banking sector capitalization. Our focus on capitalization is motivated, on the one hand, from a monetary policy perspective. The litera- ture on the bank lending channel has emphasized the importance of banks’ financial health, and capitalization in particular, as an important driver in the transmission of monetary policy shocks (Kishan and Opiela, 2000). The importance of the bank lending channel in Germany is documented in, among others, Kakes and Sturm (2002). On the other hand, from a financial stability perspective, capital regulations have been at the center of banking regulations through- out our sample period. Moreover, capitalization is one of the most important determinants of bank distress in both our sample and other countries (Wheelock and Wilson, 2000; King et al., 2006).
F. De Graeve et al. / Journal of Financial Stability 4 (2008) 205–231 225
To infer the effect of banking sector capitalization on the transmission of shocks, we simulate the system under two different initial conditions. The experiment contrasts the effect of a monetary policy shock at a time when the banking sector is poorly capitalized, with the effects of such a shock in a state where financial health (i.e. capitalization) is high. Capital is defined in terms of both our capitalization measures in the hazard model, equity and reserves. In Germany in particular, banks use mostly their reserves to adjust regulatory capital (Porath, 2006). The ‘low’ (‘high’) initial state is defined as one in which average banking sector capitalization is one standard deviation below (above) its mean. Fig. 7 compares the effect of a monetary policy shock on the probability of distress in both these states.
First note that irrespective of the state considered, distress increases significantly following the monetary policy impulse. This confirms the baseline qualitative conclusion on the existence of a trade-off. Second, quantitatively, the response in the highly capitalized scenario is much smaller relative to both the baseline model and the low-capital scenario. Monetary policy shocks have a very strong effect on banking sector distress when the latter’s financial health is poor. In particular, the effect is approximately six times as large in the poorly capitalized state relative to the well capitalized state.
From the monetary policy perspective, these findings confirm the importance of banks’ financial health in the transmission of monetary policy shocks. Potentially, higher bank distress might constrain their loan supply, either through increasing difficulties to obtain loanable funds or through restrictions imposed by the regulator. These different effects may influence the strength of the bank lending channel (Kashyap and Stein, 1995, 2000). For example, Kishan and Opiela (2000) report that poorly capitalized U.S. banks exhibit a significantly stronger loan contraction response to monetary shocks compared to large, well-capitalized banks. Note, however, that we do not model loan supply responses here explicitly and therefore caution to draw firmer inference regarding the bank lending channel.
From the financial stability perspective, the fact that resilience increases with banking sector capitalization is in line with the use of capital requirements. This is supportive of regulatory requirements imposed since the early nineties. However, even in the high capital state, we still find a significant response of banking sector distress. This also supports the recent debate about extending banking regulations beyond capital requirements. The persistent trade-off between price and financial stability paired with the potential relation to the bank-lending channel of monetary transmission highlights in our view once more the crucial need for close coordination between policy makers in charge of either component of the twin objective.
5. Conclusion
We provide in this study empirical evidence on the nexus between financial and monetary stability. Our approach rests on an integrated micro–macro model. Two main contributions are to our knowledge the first of their kind in financial stability analysis. First, we measure the financial stability directly at the bank level as the probability of distress. Second, we integrate a microeconomic hazard model for bank distress with a standard macroeconomic model. The advantage of the approach followed is that it incorporates micro information, allows for non- linearities and allows for general feedback effects between financial distress and the real economy. Our analysis is based on German bank and macro data between 1995 and 2004. Our main findings are as follows.
We find evidence of a trade-off between the two main objectives of central banks: monetary and financial stability. An unexpected tightening of monetary policy by one standard deviation
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increases the average probability of bank distress by 0.44% after 1 year. While we point out that inference regarding the exact timing of dynamics remains subject to care due to data limitations, the magnitude of this trade-off is robust to an alternative specification of the model in quarterly periodicity akin to Jacobson et al. (2005).
This significant disturbance of financial stability can not be identified if we employ a model that fails to account for microeconomic and non-linear effects. Hence, the necessity to model the intricate dynamics between macroeconomic measures targeted for (monetary) policy making and microeconomic measures of financial stability measured more directly at the bank level is confirmed.
The distinction of responses for different banking sectors exhibit heterogeneous dynamics, which may reflect respectively alternative business models. Publicly owned savings banks react less significantly to a policy shock, potentially due to the refunding function fulfilled by central savings that dampens the immediate impact of monetary shocks. Instead, especially small cooperative banks exhibit pronounced responses.
The disaggregation of the baseline result into four increasingly severe distress events further suggests that absorbing failure events, such as restructuring mergers or outright closures of banks, are unlikely triggered by monetary shocks. In turn, the significant increase in the likelihood of weaker distress events underpins that monetary shocks can put banks onto the financial regulator’s watchlists.
Finally, we find that the effect of monetary policy shocks on financial stability is sub- stantially larger if bank capitalization is low. The resulting increase in distress is both statistically and economically significant and details a route through which the bank lending channel may generate real effects: an exacerbated PD response for poorly capitalized banks might imply higher re-financing costs of banks that lead to a more pronounced reduction of loan supply compared to well-capitalized banks. In that sense, our results are in line with Kishan and Opiela (2000) who also stress the importance of bank capitalization for monetary transmission.
The presence of a trade-off between monetary and financial stability has in our view another important policy implication. Among members of the European Monetary Union the man- dates for financial supervision and monetary policy are separated between national central banks and the European Central Bank, respectively. Hence, the importance of harmonized definitions of distress and, more importantly, concerted policies in the European System of Central Banks stressed by, for example Allen and Wood (2006) and Borio (2006), is corrob- orated.
Acknowledgements
We thank seminar participants at the Riksbank, Deutsche Bundesbank, and the Financial Insta- bility, Supervision and Central Banks conference organized by the Bank of Finland. Without implicating them, we thank Olivier de Bandt, Gunther Cole, Robert DeYoung, Robert Eisenbeis, Giorgio di Giorgio, Rocco Huang, Tor Jacobson, Jesper Lindé, Kasper Roszbach, Rudi Vander Vennet, as well as our discussant Pierre Siklos and an anonymous referee for most helpful com- ments. Michael Koetter acknowledges financial support from the Netherlands Organization for Scientific Research NWO. This paper is part of a research project sponsored by the foundation ’Geld und Währung’. The paper represents the authors’ personal opinions and not necessarily those of the Deutsche Bundesbank. We are grateful to the Bundesbank for the provision of data. Any remaining errors are, of course, our own.
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Appendix A
See Tables A.1–A.4.
Table A.1 Mean CAMEL covariates per banking group and distress category
Variable All Banking groups Distress category
Com’cl Sav’s Coop’s I II III IV
Equity ratio, c1 8.45 14.67 7.64 8.20 9.98 7.77 7.54 8.22 Total reserves, c2 0.93 0.21 1.39 0.86 0.48 0.72 0.36 0.44 Customer loans, a1 11.13 13.12 11.13 11.03 13.58 12.98 15.38 13.83 Off-balance sheet, a2 3.14 6.49 2.78 2.96 3.00 3.07 3.96 3.62 Size, a3 19.22 20.16 20.68 18.65 19.63 19.20 19.24 19.03 RoE, e1 14.80 7.68 19.08 14.18 1.08 7.30 1.46 2.99 Liquidity, l1 6.70 11.35 4.43 7.04 8.71 7.69 7.92 7.63 Change in real GDP, m1 1.70 1.67 1.66 1.72 1.56 1.56 1.73 1.79 Inflation, m2 0.92 0.95 0.91 0.92 0.82 0.68 0.89 0.65 Interest (3 months), m3 3.79 3.80 3.77 3.80 3.84 3.59 3.78 3.69 Observations 26012 1509 5569 18736 88 446 252 347
All variables measured in percent except size; c1: core capital to risk-weighted assets; c2: reserves to total assets; a1: customer loans to total assets; a2: off balance sheet activities to total assets; a3: log of total assets; e1: return on equity; l1: net interbank assets and cash to total assets.
Fig. A.1. Evolution of bank-specific, distress, and macroeconomic covariates.
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Table A.2 Logit model parameters per banking groups and distress categories Variable All Banking groups Distress categories
Com’cl Sav’s Coop’s I II III IV
Equity ratio −0.0787*** (0.0173) 0.0174 (0.0119) −0.1949** (0.0983) −0.1320*** (0.0247) 0.0130 (0.0234) −0.1346*** (0.0274) −0.1536*** (0.0367) −0.0608** (0.0266) Total reserves −0.7558*** (0.0859) −0.6941* (0.4134) −0.8506*** (0.2007) −0.6644*** (0.1067) (0.2734) −0.2981*** (0.0756) −1.5298*** (0.4497) −1.2238*** (0.1549) Customer loans 0.0224*** (0.0028) 0.0053 (0.0070) 0.0465*** (0.0130) 0.0203*** (0.0036) 0.0166* (0.0086) 0.0210*** (0.0046) 0.0292*** (0.0054) 0.0193*** (0.0048) Off-balance sheet −0.0038 (0.0095) −0.0247 (0.0205) 0.0192 (0.0737) −0.0010 (0.0138) −0.0727* (0.0389) −0.0361** (0.0184) 0.0181 (0.0164) 0.0124 (0.0131) Size −0.0547*** (0.0212) 0.0117 (0.0916) −0.1688 (0.1408) 0.1595*** (0.0343) 0.1462** (0.0622) −0.0558* (0.0325) −0.0614 (0.0378) −0.1516*** (0.0404) RoE −0.0411*** (0.0022) −0.0108** (0.0054) −0.0598*** (0.0091) −0.0443*** (0.0030) −0.0354*** (0.0047) −0.0327*** (0.0026) (0.0037) −0.0377*** (0.0029) Liquidity 0.0286*** (0.0052) −0.0005 (0.0085) 0.1110*** (0.0382) 0.0380*** (0.0080) 0.0161 (0.0124) 0.0363*** (0.0074) 0.0327*** (0.0092) 0.0156* (0.0095) Change in real GDP −0.2988*** (0.0800) −0.0016 (0.3148) −0.3749 (0.3436) −0.2584*** (0.0865) −1.4865*** (0.2825) −0.5429*** (0.1219) 0.0953 (0.1679) −0.0295 (0.1447) Inflation −0.5222*** (0.0731) −0.4397 (0.2735) −0.7368*** (0.2859) −0.4378*** (0.0806) −1.4000*** (0.2565) −0.7782*** (0.1112) −0.0323 (0.1591) −0.4512*** (0.1259) Interest (3 months) 0.2117** (0.1035) 0.2068 (0.3801) 0.3133 (0.4522) 0.1491 (0.1109) 1.9196*** (0.4018) 0.3566** (0.1624) −0.2239 (0.2157) −0.0538 (0.1797) Constant −0.7354 (0.5122) −3.7112* (2.1470) 1.1132 (3.1157) −4.2133*** (0.7673) −11.3544*** (1.6585) −1.4457* (0.7953) −0.8691 (0.9941) 0.5311 (0.9161) Observations 26012 1509 5569 18736 24967 25325 25131 25226 R-squared 0.1133 0.0405 0.2031 0.1206 0.1218 0.068 0.1515 0.1199 AURa 0.7741 0.6641 0.8443 0.7796 0.8354 0.7395 0.8501 0.7963
Notes: Robust standard errors in parentheses;∗∗∗,∗∗,∗ denote significant at the 1%,5%,10% level, respectively. For variable descriptions see Table A.1. a Area under the Receiver Operating Characteristics curve (Hosmer and Lemshow, 2000).
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Table A.3 Logit model neglecting macroeconomic covariates Variable All Banking groups Distress categories
Com’cl Sav’s Coop’s I II III IV
Equity ratio −0.0751*** (0.0171) (0.0117) −0.2346** (0.1005) −0.1246*** (0.0245) 0.0107 (0.0241) −0.128*** (0.0267) −0.1497*** (0.0367) −0.0562** (0.0257) Total reserves −0.6885*** (0.0827) −0.7207* (0.4097) −0.7636*** (0.1903) −0.5939*** (0.103) −0.8495*** (0.2674) −0.2148*** (0.0726) −1.4978*** (0.4379) −1.1476*** (0.1476) Customer loans 0.0188*** (0.0028) 0.0059 (0.0072) 0.0306** (0.0125) 0.0164*** (0.0035) 0.0144 (0.0088) 0.0158*** (0.0047) 0.0274*** (0.0054) 0.0156*** (0.0048) Off-balance sheet −0.0108 (0.0101) −0.0294 (0.0205) 0.0149 (0.0733) −0.0067 (0.0145) −0.0935** (0.0432) −0.0476** (0.0196) 0.0153 (0.0168) 0.0065 (0.0137) Size −0.0315 (0.0206) 0.016 (0.0916) −0.167 (0.1363) 0.199*** 0.0334 0.191*** (0.0608) −0.0206 (0.0312) −0.052 (0.0369) −0.1309*** (0.0387) RoE −0.043*** (0.0022) −0.008 (0.0051) −0.0621*** (0.009) −0.0466*** (0.0029) −0.0387*** (0.0043) −0.0354*** (0.0024) −0.0382*** (0.0035) −0.0387*** (0.0028) Liquidity 0.0287*** (0.0052) −0.0008 (0.0085) 0.102*** (0.0398) 0.039*** (0.0078) 0.0224** (0.0109) 0.0382*** (0.0073) 0.0313*** (0.0092) 0.012 (0.0098) Constant −1.3072** (0.5122) −3.3692 (2.147) 1.5279 (3.1157) −5.2177*** (0.7673) −8.5205*** (1.6585) −2.3024*** (0.7953) −1.764* (0.9941) −0.4521 (0.9161) Observations 26,012 1,509 5,569 18,736 24,967 25,325 25,131 25,226 R-squared 0.103 0.024 0.188 0.113 0.095 0.051 0.149 0.106 AURa 0.766 0.623 0.839 0.772 0.826 0.723 0.850 0.784
Notes: Robust standard errors in parentheses;∗∗∗,∗∗,∗ denote significant at the 1%,5%,10% level, respectively. For variable descriptions see Table A.1. a Area under the Receiver Operating Characteristics curve (Hosmer and Lemshow, 2000).
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Table A.4 Quarterly and annual hazard parameters compared
Quarterly Annual
Equity ratio −0.096*** (0.0159) −0.0787*** (0.0173) Total reserves −0.631*** (0.072) −0.7558*** (0.0859) Customer loans 0.008*** (0.003) 0.0224*** (0.0028) Off-balance sheet −0.031*** (0.0102) −0.0038 (0.0095) Size −0.049*** (0.017) −0.0547*** (0.0212) RoE −0.031*** (0.001) −0.0411*** (0.0022) Liquidity 0.034*** (0.004) 0.0286*** (0.0052) Change in real GDP −0.603*** (0.046) −0.2988*** (0.0800) Inflation −0.279** (0.119) −0.5222*** (0.0731) Interest (3 months) −0.284*** (0.037) 0.2117** (0.1035) Constant −0.691 −0.7354 (0.5122)
0.425 Observations 111656 26012 R-squared 0.082 0.1133 AURa 0.7559 0.7741
Quarterly logit model of bank distress. Bank-specific covariates are lagged by four quarters as in Jacobson et al. (2005). Coefficients for macroeconomic covariates denote cumulative effects. Notes: Robust standard errors in parentheses;∗∗∗,∗∗,∗denote significant at the 1%,5%,10% level, respectively. For variable descriptions see Table A.1.
a Area under the Receiver Operating Characteristics curve (Hosmer and Lemshow, 2000).
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- Monetary policy and financial (in)stability: An integrated micro-macro approach
- Introduction
- The data
- Methodology and auxiliary results
- A microeconomic measure of financial stability
- The macroeconomic model
- The integrated micro-macro model
- The reduced form
- The structural form
- Periodicity of distress
- Results
- The aggregate response
- The importance of accounting for micro and non-linearity aspects
- Is it the data?
- Dissecting the evidence: types of banks
- Dissecting the evidence: types of distress
- Banking sector capitalization and the resilience to shocks
- Conclusion
- Acknowledgements
- Appendix A
- References
Monetary-policy-and-financial-stability-What-role-for-the-futures-market-_2006_Journal-of-Financial-Stability.pdf
Journal of Financial Stability 2 (2006) 95–112
Monetary policy and financial stability: What role for the futures market?
John Driffill a, Zeno Rotondi b, Paolo Savona c, Cristiano Zazzara d,∗ a Birkbeck College, University of London, UK
b Capitalia Banking Group, University of Ferrara, Italy c University “Luiss-Guido Carli” of Rome and Scuola Superiore della Pubblica Amministrazione, Italy
d Capitalia Banking Group, University “Luiss-Guido Carli” of Rome, École Polytechnique Fédérale de Lausanne, Italy
Received 4 October 2004; accepted 1 March 2005 Available online 2 March 2006
Abstract
This paper examines interactions between monetary policy and financial stability. There is a general view that central banks smooth interest rate changes to enhance the stability of financial markets. But might this induce a moral hazard problem, and induce financial institutions to maintain riskier portfo- lios, the presence of which would further inhibit active monetary policy? Hedging activities of financial institutions, such as the use of interest rate futures and swap markets to reduce risk, should further pro- tect markets against consequences of unforeseen interest rate changes. Thus, smoothing may be both unnecessary and undesirable. The paper shows by a theoretical argument that smoothing interest rates may lead to indeterminacy of the economy’s rational expectations equilibrium. Nevertheless, our empiri- cal analysis supports the view that the Federal Reserve smoothes interest rates and reacts to interest rate futures. We add new evidence on the importance for policy of alternative indicators of financial markets stress. © 2006 Elsevier B.V. All rights reserved.
JEL classification: E44; E52; E58; G12; G13
Keywords: Central bank; Interest rate rule; Monetary policy; Financial stability; Macroeconomic stability; Asset prices; Stock market; Credit spread; Futures market; Hedging; Basis risk; Federal Reserve
∗ Corresponding author. Fax: +39 06233200807. E-mail addresses: [email protected] (J. Driffill), [email protected], [email protected]
(Z. Rotondi), [email protected], [email protected], [email protected] (C. Zazzara).
1572-3089/$ – see front matter © 2006 Elsevier B.V. All rights reserved. doi:10.1016/j.jfs.2005.03.001
96 J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112
1. Introduction
Central banks in the developed world have, in the last 10 or 15 years, overwhelmingly switched to a policy of setting short-term interest rates with the primary aim of targeting inflation. Other objectives allegedly remain, but occupy a lower place on the agenda. Among them is the objective of maintaining financial stability, the responsibility for which has long been a role of central banks. The survival of this role has been cited in support of the empirical finding that interest rates seem to move gradually in response to changes in macroeconomic conditions (notably the output gap and inflation). It is argued that by making interest rate changes smaller and more predictable, central banks reduce the volatility of the profits of commercial banks and reduce the risk of bank insolvencies and insolvencies among the businesses who borrow from them.1
With the passage of time, and the growth in the sophistication of financial markets and in the range of financial instruments available for trading risks, banks like other players in these markets have become increasingly well able to hedge against the risks that variable short-term interest rates pose for their profits and balance sheets. They have turned to markets in interest rate futures and more recently to interest rate swaps in order to hedge their positions. These activities should in principle have reduced banks’ exposure to such risks. Nevertheless, the possibilities for hedging are less than perfect. Unanticipated changes in interest rates have residual effects on bank profits, and central banks may continue to moderate their interest rate changes for reasons of stability of financial markets.
The purpose of this paper is to explore the interaction of monetary policy and financial stability, and in particular to examine the role played by financial institutions’ use of futures and other derivatives markets to hedge risks. Research on the subject of monetary policy and financial stability has mostly focused its attention on central banks’ alleged practice of smoothing interest rate movements (see Goodfriend, 1987, and more recently Smith and van Egteren, 2004). It is argued that lower volatility should reduce bank insolvencies caused by unanticipated sharp increases in short-term interest rates. Widespread use of hedging by banks should further reduce their vulnerability to interest rate fluctuations, and enable central banks to change interest rates with less caution. Nevertheless, the residual risk – basis risk and other risks that remain after imperfect hedging opportunities have been exploited – may act as a moderate restraint on monetary policy.
It is possible that the macroeconomic stability obtained as a result of aggressive use of monetary policy brings its own dangers. It may induce a form of moral hazard. Commer- cial banks and other financial institutions may respond to a stable macroeconomic climate by taking on riskier portfolios of loans and deposits than are consistent with financial stabil- ity. Markets may act on what they believe to be an implicit guarantee of public policy that will maintain stability and possibly bail them out of difficulties. The Federal Reserve (see, for instance, Poole, 2004) is alive to these dangers and keen to avert them by making markets aware that risks of instability exist, and that the Federal Reserve would not be able to bail out large players.
Our study makes two contributions. First, from a theoretical standpoint, we analyze the inclu- sion of futures prices, and the associated basis risk, in the central bank’s reaction function,
1 The relation between monetary policy and financial stability has been long debated and, as argued convincingly by Padoa-Schioppa (2002) and Schinasi (2003), central banks’ monetary policy has a natural role in ensuring financial stability.
J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112 97
extending the analysis of determinacy of equilibrium conducted by Bullard and Schaling (2002). We show the existence of a trade-off between macroeconomic and financial stability. We argue that this trade-off calls for caution, but does not necessarily imply that the central bank cannot smooth interest rates to reduce basis risk.
Second, from an empirical perspective, we assess the importance for monetary policy of the response to interest rate futures, focusing on the behaviour of the Fed. Following the same econo- metric approach as Clarida et al. (2000), we estimate an augmented interest rate rule with the stock index, the credit spread and the eurodollar futures rate in addition to inflation and output gap. Our empirical findings support the importance of futures market movements, and in particular of the stabilization of basis risk for the Federal Reserve’s monetary policy.
This is an interesting result since the extant literature has mainly stressed the importance of the inclusion of stock market index (Sack and Rigobon, 2003; Chadha et al., 2004; Rotondi and Vaciago, 2005) and the credit spread (Castelnuovo, 2003; Gerlach-Kristen, 2004) in the Fed’ s interest rate rule.
The paper is organized as follows. Section 2 defines the concept of financial stability from the perspective of central banks. Section 3 examines the role of interest rate futures markets, and the use of other derivatives, as part of banks’ policies for hedging risk. It considers implications for financial stability. Section 4 presents a theoretical analysis of the explicit inclusion of futures prices in the central bank’s reaction function within a New Keynesian framework. Section 5 measures the response to future prices of the Fed’s monetary policy, while Section 6 concludes.
2. Definitions of financial stability
Before exploring the nexus between monetary policy and financial stability, it is useful to provide some definitions and highlight the role played by the futures market.
While financial stability is undeniably an important concept that policy makers aim to strive for, the term does denote different (albeit related) meanings to different commentators on the topic. Indeed, researchers on the topic have found it more useful and convenient to analyze financial stability based on its negative counterpart, financial instability, as it probably is easier to identify situations of financial instability and their possible causes.
With respect to financial instability, however, the definitions proposed have been diverse, depending on the focus of the research. Focusing on the role of asymmetric information in inducing financial instability, Mishkin (1999) defines financial instability as a disruption to the efficiency of financial system in fund allocation by ways of worsening adverse selection and moral hazard. Concentrating on the balance sheet channel through the net worth positions of borrowers, Bernanke and Gertler (1987) defines financial fragility as a situation in which potential borrowers have low wealth relative to the size of their projects. Such a situation causes high agency costs and impairs performance in investment sector and in the economy as a whole. The IMF (2003), on the other hand, focuses on different types of “seizures” within the financial system and takes periods of financial instability to be periods of severe financial market disruptions that the system’s ability to provide payment services, to price and transfer risk, and to allocate credit and liquidity is impaired and then potentially leads to a reduction in real activity.
While definitions above put emphasis on the underlying mechanics of financial instability, other definitions focusing on the symptoms of financial instability have also been proposed (see Issing, 2003 for discussion). Symptoms of financial instability are often reflected by asset price volatility, distresses in financial institutions, and affected output performance. Crockett (1997) thus defines financial instability as a situation in which economic performance is potentially
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impaired by fluctuations in the price of financial assets or in the ability of financial inter- mediaries to meet their contractual obligation. Bernanke and Gertler (1999) define financial instability as being synonymous with asset price volatility, which takes price far away from its fundamental level, before finally reversing suddenly and violently in a “crash”. Ferguson (2003), on the other hand, defines financial instability as a situation characterized by three basic criteria: (1) some important set of financial asset prices seem to have diverged sharply from fundamental; and/or (2) market function and credit availability, domestically and perhaps internationally, have been significantly distorted; with the results that (3) aggregate spending deviates (or is likely to deviate) significantly, either above or below, from the economy’s ability to produce.
While there have been many proposed definitions of financial instability that are useful in various analytical contexts, a useful and practical definition of financial instability from monetary policy decision’s point of view should be framed with the root cause of the instability in mind. At gist, we may affirm that financial instability arises because of excessive financial risk taking by economic agents, be it consumers, investors, the government, or intermediaries themselves. As consumers, investors, or the government accumulate more debts, their ability to repay the full amount of debt diminishes, ceteris paribus. The inability of borrowers to repay their debt by the full amount means that lenders, often banks, will have to shoulder losses. If the banks cannot shoulder such losses using their retained profits, they will need to draw upon owners’ capital. By drawing upon owners’ capital to cover the losses on the balance sheets, the banks will have less capital to support other existing loans. Recalls of existing loans (possibly unrelated to those already gone sour) will be made. In that case, intermediary functions of the banks will be severely disrupted as banks start to draw back loans from the economy rather than granting new ones. The recalls of loans can make matter worse as they could instigate a disruption in real economic activities, which could result in more loans turning bad and more losses to cover. Ultimately, excessive financial risk taking that result in losses on bank balance sheets could lead to a drastic systemic disruption in the functioning of the whole banking system, and possibly later result in widespread economic failures. Financial instability is thus caused by build-ups of financial imbalances that put great risks on the intermediaries’ balance sheets to the extent that the financial system can no longer allocate funds efficiently. Defining financial instability as above and focusing mainly on banks can help the process of framing monetary policy decision more clear-cut.2
Focusing on the importance of the banking system from a financial stability perspective, a fur- ther definition of financial instability may be related to banks’ interest rate risk hedging policies. In the words of Freixas and Rochet (1997), a bank is “. . . an institution whose current opera- tions consist in granting loans and receiving deposits from the public”. Such traditional form of intermediation leaves banks open to interest rate exposure and to duration or maturity mismatch exposure, which arises when banks borrow short and lend long. The greater the amount of interest rate risk banks will incur and the greater the increased risk in terms of financial stability. Therefore, effective hedging of interest rate risk is highly important both to the banks and to the financial system as a whole as it will reduce the banks’ exposure to volatile interest rate movements. This will lessen the likelihood of extreme fluctuations in a bank’s financial condition and reduce the probability of a bank becoming insolvent (Brewer et al., 2001).
2 Although we only refer to banks, the analysis and definition here are applicable to other non-banks financial interme- diaries.
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3. The importance of the futures market for financial stability: the case of financial institutions
The smoothing of interest rates by central banks is widely documented. It manifests itself in the appearance of the lagged dependent variable in estimated Taylor Rules, in which the interest rate used for monetary policy is explained in terms of inflation rates and the output gap. It is often suggested that one of the many possible reasons for this apparent smoothing is to preserve the stability of financial markets. By responding slowly over a period of several months to some change in macroeconomic conditions, the central bank reduces the size of unanticipated changes in short-term interest rates to which the commercial banks and other participants in financial markets are subjected. This reduces the chance that a bank’s profits from its loan portfolio will be put under pressure or that its balance sheet will be weakened. This argument is often accepted uncritically. However, it should perhaps be scrutinized more closely.
The argument that central banks are concerned about financial stability, and that this concern colours their interest rate decisions, stems from the potentially serious consequences of instability. If a commercial bank were to find itself insolvent or illiquid, causing it to default on its payment obligations, it could send a shock through the whole financial system, causing other institutions to suffer losses resulting from their claims on customers of the defaulting bank, or perhaps through inter-bank lending with that particular institution. This possible sequence of events could jeopardise the stability of the entire economy.
The reason that interest rate changes, particularly rises in short-term policy rates may damage banks’ profits is that banks allegedly borrow short and lend long. The consequences of such a maturity mismatch could in principle be serious. For example, a sudden inflation scare might cause a shock to the term structure of interest rates, induce a tightening of monetary policy, and thereby a sharp inversion of the yield curve. A commercial bank might be committed to funding loans for a period of time into the future at the earlier lower interest rate balanced by deposits, which it must accept at the new higher interest rate. This will have an adverse effect on the bank’s profits and capital ratio and increase the likelihood of insolvency.
To some degree this is true: banks borrow short and lend long. Many deposits are held in checking accounts and may be withdrawn on sight. Bank loans typically have a longer term. However, maturity transformation has been the stock-in-trade of commercial banks for centuries, and they employ well-known methods for dealing with the risks posed by interest rate movements. Overdraft facilities or lines of credit are often made at variable interest rates, so while borrowers can be confident of the amount available to borrow, the interest rate they pay may be varied at very short notice, and effectively the risk of movements in short-term interest rates is passed to the borrowers. Fixed term loans are generally made at rates that allow for default risk and also for the illiquidity of the loan from the lender’s viewpoint. North American banks, in common with banks in other countries with the Anglo-Saxon banking traditions, resist making substantial long-term loans at fixed interest rates. These tend to constitute a relatively small fraction of their loan portfolios.
There have in the past been episodes in which interest rates have risen rapidly, which have not caused major problems for banks or financial instability. During the 1970s, interest rates rose strongly. During the period between 1979 and 1982, when the United States experimented with monetary base control, interest rates were both high in nominal terms, and very volatile. While the experience produced loud complaints from the financial markets it did not lead to financial instability. Consequently, historical experience suggests that the US banking system can withstand substantial changes in interest rates without danger of financial instability. The collapse of the
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savings and loan associations in the 1980s is arguably a separate issue. It resulted from the removal of interest rate ceilings, under the shelter of which those institutions had accumulated fixed-interest loans. This combined with other aspects of the regulatory regime that followed induced excessive risk-taking by savings and loans, many of which deliberately courted bankruptcy. So the savings and loan debacle can be viewed as a consequence of catastrophic regulatory failure.
Financial institutions have increasingly used derivatives as part of their strategy for managing exposure to risks of interest rate movements. Banks can use interest-rate-related derivatives to hedge maturity mismatch. In recent years the variety of these products and the liquidity of the markets in which they are traded have increased. Whereas, interest rate futures were initially the dominant choice, interest rate swaps have now become the most widely used instrument. It is likely that less volatile interest rates in world markets have contributed to this shift. When interest rates are highly volatile, futures are a more effective method of hedging, given the uncertainty in the underlying product and the unwillingness of a counterparty to accept a converse position as is required with swaps. In recent years as interest rates have become less volatile the environment has become more conducive to swaps trading. With less volatile interest rates, banks are able to judge their interest rate exposure for a period of time in the future more accurately. This makes it easier for two counter-parties to enact a swap agreement, as they are more confident in their judgement of future interest rate movements, and wild swings in interest rates are less likely.
However, interest rate futures and swaps may not remove all the risk arising from maturity mismatch. The hedging instruments available do not permit banks to insure precisely against fluctuations in the rate on interest they pay on short-term deposits and reserves, which is closely related to, but not identical to, the Federal Funds rate in the United States. They may be able to use futures markets to swap interest payments based on LIBOR for those based on the average federal funds rate over the same 3-month period. But if their cost of deposits fluctuates relative to the Federal Funds rate, they remain exposed to the risk of these fluctuations, and full hedging may not be optimal in this case anyway. This residual risk is known as basis risk.
These arguments strengthen the view that the risks to financial stability posed by movements in short-term interest rates in the United States are small, and they should therefore, have only a small influence on the interest rate setting decisions of the Federal Reserve. Nevertheless, the residual risks may induce some caution on the part of the Fed.
But at this point another argument comes into play. While in the short term cautious interest- rate changes by the Fed may enhance financial stability, in the longer term they may do less to enhance it and may work in the other direction to reduce it. The achievement of low and stable inflation by the Fed, since the mid 1980s, has arguably produced economic conditions conducive to low and stable interest rates. However, it was achieved by the vigorous use of monetary policy. It may be necessary for central banks to be free to make big changes in policy in the face of large shocks in order to maintain stability in the medium term.
If the Federal Reserve were to limit changes in interest rates to protect banks’ balance sheets, banks may feel they have some implicit insurance, inducing a moral hazard problem. Banks may feel able to operate on thinner margins and with riskier portfolios of assets and liabilities. Consequently it may be argued that robust regulation of financial markets is the appropriate response, rather than a smoothing of interest rate changes, to ensure that banks operate with sufficient margins of capital and liquid reserves, so that they can withstand the consequences of all but the most extreme fluctuations in market conditions.
That the Federal Reserve is concerned that participants in financial markets should not behave as though there were an implicit guarantee against their failure is illustrated by a recent speech given by the President of the Federal Reserve Bank of St. Louis, William Poole (2004). In this
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Poole is clearly concerned that markets do not price the risk posed by the fact that the large US Government sponsored financial institutions (the GSEs) like the Freddie Mac, Fannie Mae, and others, maintain excessively thin capital positions, making them more vulnerable to shocks. He clearly points out that they would be allowed to fail in a crisis. This market misperception of risk worsens the problem by providing the GSEs with excessively cheap funds and allowing them to grow too rapidly.3 This underlines the original point that financial stability remains a concern for central banks and that it may therefore, affect their setting of interest rates.
4. Monetary policy and futures market movements
In this section we provide a theoretical analysis in order to explore the nexus between monetary policy and the futures market. Particularly, we focus on potential risks to macroeconomic stability stemming from the response of monetary policy to futures prices movements.
The link between monetary policy and asset price movements has been of perennial interest to policy makers and academic researchers. One of the main area of research focuses on the view that asset prices may affect real activity. The channels of the transmission mechanism from asset prices to economic activity are mainly three: households’ wealth effect on consumption expenditure (Modigliani, 1971); Tobin’s Q effect on investment (Tobin, 1969); financial accelerator effect on investment (Bernanke and Gertler, 1989).
These three channels are undoubtedly important in affecting both output and inflation, but it is less clear whether they provide a strong argument for basing monetary policy on asset prices movements. In fact, it has been argued that the gain of including asset prices in monetary policy rules in practice adds little to stabilizing output and inflation.4 This is due to the fact that asset channels are similar to aggregate demand channels, as they tend to increase both output and inflation. Thus, inflation targeting yields most of the gains of adopting asset price targeting without the drawbacks of the appearance of interfering in the working of financial markets.
On the other hand, asset prices seem to display exogenous movements unrelated to the under- lying state variables. There exist several historical examples that show that extreme movements in asset prices have coincided with prolonged periods of macroeconomic instability.5 This raises the question of what can central banks do in order to minimize the likelihood of asset price mis- alignments. However, even if one accepts the role of asset prices in the propagation of shocks, asset price misalignments are difficult to detect. The problem is that asset prices are too volatile and too unrelated to real activity, as argued for instance by Gertler et al. (1998).
Nevertheless, the above concern about the ability to detect asset price misalignments by central banks calls for caution and does not necessarily imply that we should ignore them. As Cecchetti et al. (2000) observe, the difficulties associated with measuring asset price misalignments are not substantially different from those related to potential GDP or the equilibrium real interest rate. Actually, Borio and Lowe (2002) argue that what really matters for monetary policy is not to respond to asset price bubbles per se, but rather to reduce the risk of financial distress resulting from the occurrence of financial imbalances. In particular, they show that identifying
3 Poole remarks: “their [the GSEs] growth incentives insure that their scale will increase over time, unless they become subject to full private market incentives through convincing federal policies that lead to market recognition that the federal government will not guarantee GSE obligations in a crisis.”
4 In the literature this point has been particularly stressed by Bernanke and Gertler (1999, 2001) and Gilchrist and Leahy (2002).
5 See Cecchetti et al. (2000) for an analysis of the major economic episodes of asset price misalignments.
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ex ante financial imbalances is difficult but not impossible. By using data from a large number of countries they have obtained empirical evidence showing that the simultaneous surge in both credit and asset prices provides a relatively reliable warning of financial imbalances ahead.
Here, in order to explore further the issue of including explicitly asset prices in the central bank’s reaction function we consider the analysis of determinacy of rational expectations equilibrium provided by Bullard and Mitra (2002) and Woodford (2003). In fact, as shown by Bullard and Schaling (2002), introducing asset prices in the central bank’s interest rate rule may weaken the requirement for determinacy of the rational expectations equilibrium and potentially lead to macroeconomic instability. They have shown this result for the case of equity prices. In the present analysis we consider instead the case of futures prices.
4.1. The model
In the present framework the supply function is given by a New Keynesian Phillips curve that relates inflation positively to the output gap:
πt = λyt + βEtπt+1, (1) where β is the discount factor considered in the discounted sum of utilities of a representative household, with 0 < β < 1.
We have also an IS equation which relates inversely the output gap to the real interest rate:
yt = Etyt+1 − σ(rt − rnt − Etπt+1), (2) where σ > 0 measures the intertemporal elasticity of substitution of aggregate expenditure.
The model represents a log-linear approximation of the equilibrium conditions under a deter- ministic steady state. Hence, all variables are expressed as a log-deviation from their long run level. The nominal short-term interest rate rt is the instantaneous interest rate or continuously compounded interest rate and empirically could be approximated by the Fed funds rate. Thus, if Rt is the gross nominal interest rate on a risk-free one-period bond, then rt = log Rt. We assume absence of arbitrage opportunities and complete financial markets.
Following Bullard and Mitra (2002), we assume that the natural rate of interest rnt is an exoge- nous stochastic term that follows an AR(1) process given by
r n t = ωrnt−1 + εt, (3)
where 0 < ω < 1 and εt is an iid disturbance with variance σ 2 ε and mean zero.
Monetary policy is formulated in terms of a feedback rule for setting the nominal short-term interest rate of the following form:
rt = ρrt−1 + φπEtπt+1 + φyyt + φBR[(log P At − log Ft ) − (log P A∗ − log F ∗)], (4) where Ft is the futures price and P
A t is the price of the asset underlying the futures contract.
Here, in order to simplify the analysis, we assume that the central bank stabilizes the ratio of P At over Ft, instead of the spread. Obviously, this simplification does not affect the results. The superscript (*) indicates trend value, while the subscript BR stems for basis risk. The coefficient ρ, with 0 < ρ < 1, measures the degree of inertia in the central bank’s response to macroeconomic and financial shocks.
According to the policy rule (4), the central bank is concerned about the deviation of the current spread between futures price and asset price from its long run equilibrium level. It is important to
J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112 103
observe that the spread considered above is an ex post measure related to basis risk in a hedging situation. If we consider a hedge put in place at time t − 1, the hedging risk is the uncertainty associated with the spread realized at time t and is termed as basis risk. When the price of the asset increases by more (less) than the futures prices, the basis increases (decreases). This is referred to as a strengthening (weakening) of the basis.
Now, if we consider a one-period futures contract, it is possible to show that the central bank by setting the short-term interest rate according to (4) may affect the basis risk by smoothing the basis over time. In order to see this we introduce the assumption that futures and forward prices are perfect substitutes.6 This implies that
Ft = P At elog Rt . (5) From (5) follows that
log P At − log Ft = − log Rt ; log P A∗ − log F ∗ = − log R∗. (6) Substituting (6) back into expression (4) and using the definition of the instantaneous rate we get
rt = ρrt−1 + φπEtπt+1 + φyyt − φBRrt. (7) From (7) we obtain the following policy rule
rt = Φρrt−1 + ΦπEtπt+1 + Φyyt ; (8) with
Φρ = ρ
1 + φBR ; Φπ =
φπ
1 + φBR ; Φy =
φy
1 + φBR . (9)
Obviously the effect of modeling the concern for financial stability in this way is to reduce the response of the interest rate both to its own lagged value and also to its macroeconomic determinants. From (8) it is possible to see that as φBR → +∞ the interest rate, and hence the basis, tends to zero.7 Clearly, φBR → +∞ implies monetary policy following an interest rate peg without reaction to inflation deviations or the output gap. Accordingly, rational agents expecting this behavior from the central bank will find the basis risk reduced and close to zero.
4.2. Determinacy of equilibrium
Following Woodford (2003) and Bullard and Mitra (2002), the determinacy conditions for the model constituted by (1)–(3), (8) and (9) should be derived from the following system
Etzt+1 = Azt + arnt , (10) where zt = [πt, yt, rt−1]′, and
A ≡
⎡ ⎢⎣
β−1 −β−1λ 0 σβ−1(Φπ − 1) 1 + σ[Φx − β−1λ(Φπ − 1)] σΦρ
β−1Φπ Φy − β−1λΦπ Φρ
⎤ ⎥⎦ , a ≡
⎡ ⎢⎣
0
−σ 0
⎤ ⎥⎦ . (11)
6 See for instance Hull (2000) for a discussion on the validity of this assumption. 7 Recall that all variables are expressed as log-deviations from their trend level and constants are omitted for simplicity.
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In (10) there is a single predetermined state variable, namely rt−1, so that the equilibrium is determinate if and only if A has exactly two eigenvalues outside the unit circle. As shown by Woodford (2003), the necessary and sufficient conditions for rational expectations equilibrium to be unique are:
Φπ + 1 − β
λ Φy > 1 − Φρ, (12)
and
Φπ < 1 + Φρ + 1 + β
λ [Φy + 2σ−1(1 + Φρ)]. (13)
The condition (12) is the generalization of the basic ‘Taylor principle’ appropriate for the case at hand.8 After substituting (9) in the conditions (12) and (13) we get
φπ
1 + φBR + φy(1 − β)
(1 + φBR)λ > 1 − ρ
1 + φBR , (14)
and
φπ
1 + φBR < 1 + ρ
1 + φBR + 1 + β
λ
[ φy
1 + φBR + 2σ−1
( 1 + ρ
1 + φBR
)] . (15)
4.3. Main findings
When conditions (12) and (13) fail, the rational expectations equilibrium is indeterminate. Thus, an interesting question to ask is the following. Consider fixed values of φρ, φπ, φy, satisfying the requirement for determinacy of the equilibrium, and assume that the central bank considers to begin including a reaction to futures price movements in its policy rule what are the implications for the conditions (12) and (13)?
We can prove the following proposition:
Proposition 1. When monetary policy is conducted so as to ensure that the short-term interest rate follows a rule of the form of (4), with given fixed values of φρ, φπ, φy > 0 ensuring the satisfaction of conditions (12) and (13), then φBR > 0 works against the satisfaction of the requirement for determinacy of the equilibrium compared to the case of φBR → 0. Proof. Multiplying both sides of the inequality (14) by (1 − ρ) we get
φπ + φy(1 − β) > 1 − ρ + φBR, (16) where it is clear that for φBR > 0 the requirement for determinacy of the equilibrium provided by condition (12) becomes stricter. On the contrary, multiplying both sides of the inequality (15) by (1 − ρ) we can see that for φBR > 0 the requirement for determinacy of the equilibrium provided
8 The principle that interest rate rules should respond more than one for one to changes in inflation is called ‘Taylor principle’: see for instance Walsh (2003). However, Bullard and Mitra (2002) and Woodford (2003) have shown that in general the necessary and sufficient condition required for stability may have a more complex form than that expressed by the Taylor principle. In particular it is possible to show that Φπ > 1 is only a necessary condition for the determinacy of the rational expectations equilibrium, and even values of 0 < Φπ < 1 can be consistent with stability. However, as argued by Woodford (2003, p. 254) the Taylor principle continues to be a crucial condition for determinacy if it is reformulated as: “[. . .] At least in the long run, nominal interest rates should rise by more than the increase in the inflation rate”.
J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112 105
by condition (13) becomes less binding. Thus, in the case of φBR > 0 the most relevant condi- tion (not the unique) for determinacy is (12), which as we have shown supports the proposition made. �
Proposition 1 implies that for monetary policy there exists a trade-off between macroeconomic stability and financial stability. As the relative weight φBR attached to the basis risk stabilization motive increases, the ability of achieving macroeconomic stability is reduced. An excessively high value of φBR can even compromise the achievement of macroeconomic stability by creating indeterminacy of the equilibrium, when such indeterminacy did not otherwise exist. Clearly the existence of this trade off between macroeconomic stability and financial stability calls for caution and does not necessarily imply that the central bank cannot pursue the stabilization of the basis risk.
5. Measuring the response to futures prices
This section of the paper offers an empirical analysis. It examines the Federal Reserve’s response to movements in the price of interest rate futures when it sets interest rates.
5.1. Baseline interest rate rule
The baseline interest rate rule assumes the target rate r̄t depends on the output gap (yt) and expected inflation (Etπt+4), and that the actual interest rate (rt) adjusts gradually towards the target. It may be represented as:
rt = ρrt−1 + (1 − ρ)r̄t + ωt, r̄t = φπEtπt+4 + φyEtyt ;
(17)
Constants are omitted for simplicity. The estimation approach used is the same as that of Clarida et al. (2000) for the case of the Federal Reserve.9 The data used are the Federal funds interest rate, defined as the average effective Federal funds rate over the quarter, the output gap, defined as percent deviation of actual real GDP from the potential output estimated by the Congressional Budget Office, and inflation, measured as four-quarter change in the GDP deflator.10 GMM has been used. We have used a correction for heteroskedasticity and autocorrelation of unknown form with a Newey–West fixed bandwidth, and chosen Bartlett weights to ensure positive definiteness of the estimated variance–covariance matrix.11 The instrument set includes four lags of output gap, inflation and the federal funds rate.12
9 The econometric approach used relies on the assumption that, within our short sample, short term interest rates, inflation and output gap are I(0). However, standard Dickey–Fuller test of the null that the above series are I(1) is not rejected for the US. Nevertheless, as argued for instance by Clarida et al. (1998), standard Dickey–Fuller test has lower power against the alternative of stationarity for short samples. For this reason the assumption of stationary series is standard in the empirical literature of interest rate rules, as this literature is in general based on short samples with a stable monetary regime like in our case. 10 Data on the Fed funds rate, output gap and inflation are taken from FRED II, of the Federal Reserve Bank of St. Louis. 11 The optimal weighting matrix is obtained from first-step two-stage least squares (2SLS) parameter estimates. 12 The J-test reported in the tables is the test for the validity of the instruments used. The associated statistic is distributed
as a χ2.
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Table 1 GMM estimation of alternative forward-looking Taylor rules
Baseline Baseline with serially correlated errors
Augmented with current credit spread
Augmented with lagged credit spread
ρ 0.83 (0.04) 0.71 (0.10) 0.80 (0.02) 0.78 (0.03) φπ 2.12 (0.45) 1.93 (0.49) 2.63 (0.30) 2.64 (0.31) φy 0.93 (0.20) 0.75 (0.20) 0.98 (0.10) 0.75 (0.09) φBR 2.55 (0.45) 3.45 (0.57) φCS −2.83 (0.47) −1.66 (0.41) φSM 10.41 (2.54) 16.43 (2.67) θ 0.60 (0.13)
Adj. R-squared 0.95 0.97 0.98 0.98 S.D. dep. var. 2.08 2.08 2.08 2.08 S.E. regression 0.45 0.35 0.30 0.29 J-test 0.55 0.62 0.92 0.88
Notes: Newey–West robust standard errors in parentheses. J-test is the test for overidentifying restrictions. For this test only p-values are reported. Sample period for estimation is 1987 Q4–2003 Q2. To be consistent across policy rules estimated in levels and differences, all R2 statistics are reported for the level of the Fed funds rate. The earlier end date for the sample is required for the forward-looking specification. Constants omitted for brevity.
English et al. (2003) have reformulated the basic policy rule, by the addition of a serially correlated error term, as:
rt = rt−1 + (1 − ρ)�r̄t + [(1 − ρ)(1 − θ)](r̄t−1 − rt−1) + (ρθ)�rt−1 + εt. (18) ωt = θωt−1 + εt (19)
In expression (18) the parameter ρ reflects monetary inertia (i.e. interest rate smoothing), while θ reflects the presence of serially correlated omitted variables. English et al. (2003) found both parameters significant, and thus argued that both factors are valid and important in explaining the behavior of the central bank. In this they take issue with Rudebusch (2002), who argued that monetary inertia is an illusion.
The GMM estimates obtained from (17) and (18) are reported in Table 1. The estimates of both ρ and θ are highly significant, suggesting that both partial adjustment and serially correlated errors are present. Allowing for serially correlated errors reduces the estimated degree of partial adjustment to some extent, but the effect is relatively small, with the ρ parameter falling from 0.83 to 0.71.
5.2. Augmented interest rate rule
Here we take up the argument made by Rudebusch (2002), to the effect that the presence of serially correlated errors in the interest rate rule may reflect the omission of some additional persistent, serially correlated variable or linear combination of variables. In line with the theoretical arguments made above, we add a number of variables that may reflect the effect of concerns about financial stability on interest rate setting. The variables in question are an index of the level of stock market prices, a measure of the spread between returns on US Treasury bonds and commercial bonds, and the excess of the interest rate in euro-dollar interest rate futures contracts.
The inclusion of the stock market index is widely supported in the literature. It may reflect the central bank’s desire to offset the expected effect of stock market shocks on aggregate demand
J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112 107
(Sack and Rigobon, 2003). In addition, as Cecchetti et al. (2000) have argued, reacting to asset price movements in the “normal” course of monetary policy may reduce the likelihood of bubbles forming or getting out of hand. However, Bernanke (2002) argues that, for such a policy of leaning- against-the-bubble to provide some insurance against perceived bubbles, a small increase in the interest rate should imply a corresponding smooth reduction in the likelihood or size of a bubble. Unfortunately, the existing empirical and theoretical evidence does not support such a smooth link. Following Rotondi and Vaciago (2005) we use the Wilshire 5000, instead of the Standard & Poor’s 500 or the Dow Jones, which is a broader stock market index.13 As in Chadha et al. (2004) and Rotondi and Vaciago (2005) the stock market index enters lagged in the policy rule in order to avoid the arising of the simultaneity bias identified by Sack and Rigobon (2003).14
Castelnuovo (2003) and Gerlach-Kristen (2004) have argued in favour of including the credit spread in the Federal Reserve’s interest rate rule. These authors use the current value of the spread. Using the Hausman test, Gerlach-Kristen argues that the simultaneity problem is negligible. However, as in the case of the stock market index, we will also examine the use of the lagged spread.
Finally, we have added the change of the spread between the futures rate settled in the previous quarter and the current quarterly average of the Fed funds rate. This term is related to a particular notion of basis risk for financial institutions, as discussed for instance by Sack (2004). The notion of basis risk considered for the Fed is the excess expected return of the 3-month Eurodollar deposit over the Federal funds rate. From a financial stability standpoint, the Federal Reserve might stabilize this kind of basis risk by reducing the volatility of the spread between the futures rate quoted in the previous period and the realized Fed funds rate.
Thus, we have estimated the following augmented interest rate rule:
rt = ρrt−1 + (1 − ρ)r̄t + νt, r̄t = φπEtπt+4 + φyEtyt + φSM�pSt−1 + φCS(RCBt − R10Yt ) + φBR�(rFt−1 − rt );
(20)
where pSt is the log of the quarterly average of the Wilshire 5000 index; (R CB t − R10Yt ) the
quarterly average of the credit spread, namely the spread between the Moody’s BAA corporate index yield and the 10-year US treasury note yield; rFt the rate on a eurodollar futures contract that settles 3 months ahead.15 In this case, the instrument set used for the GMM estimation includes
13 Rotondi and Vaciago (2005) examine also the inclusion of a new variable, termed as ‘Fed model’ spread, intended to capture the importance of the relationship between the stock market and the bond market for the assessment of the presence of bubbles in the stock market. They find some evidence supporting the presence of this variable in the Fed’s interest rate rule, but they show also that the response to the 1990s bubble was non-linear. Thus, given our aim of measuring the response to futures market movements, we excluded for simplicity this variable from the present empirical analysis. Anyway our sample includes a relatively long post-bubble period. 14 The first empirical analysis that addresses explicitly the issue of the response of the Fed to stock market movements is
that of Bernanke and Gertler (1999). By using monthly data, they estimate a forward-looking policy rule where the federal funds rate reacts to expected inflation and output gap as well as to the current and lagged changes in stock prices. Their findings show an insignificant reaction of monetary policy to stock market movements. However, Sack and Rigobon (2003) argue that Bernanke and Gertler’s result may be affected by the presence of a simultaneity bias due to the endogenous reaction of stock market prices to the interest rate. 15 The source of Moody’s BAA corporate index yield, 10-year government yield and Wilshire 5000 index is DATAS-
TREAM. The data on the futures rate are the same as those used in Rudebusch (2002). In this latter case quarters are defined to start at the eurodollar futures contract settlement dates which occur about 2 weeks before the start dates of the usual quarters. This choice is due to the desire to capture true one-quarter-ahead expectations. We thank Glenn Rudebusch for having kindly provided the data. Since his data end in 2000 Q2, by means of ECONWIN we have updated them to 2004 Q2.
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four lags of output gap, inflation, the Fed funds rate, the stock index, the credit spread and the futures rate.
Before estimating (20) with GMM we need to collect terms involving respect to the short-term interest rate. Simple manipulation yields the following expression
rt = [ ρ + (1 − ρ)φBR 1 + (1 − ρ)φBR
] rt−1 +
[ (1 − ρ)
1 + (1 − ρ)φBR
] r̃t + νt, (21)
with
r̃t = φπEtπt+4 + φyEtyt + φSM�pSt−1 + φCS(RCBt − R10Yt ) + φBR�rFt−1. (22) The GMM estimates obtained from (21) are reported in Table 1. Allowing for these additional variables reduces the estimated degree of partial adjustment very slightly. In Table 1 we have reported both estimates obtained with the current quarterly average of the credit spread, and also estimates obtained with the lagged credit spread for end-of-quarter data.16 In the latter case the target value for the interest rate (22) should be rewritten as
r̃t = φπEtπt+4 + φyEtyt + φSM�pSt−1 + φCS(RCBt−1 − R10Yt−1 ) + φBR�rFt−1. (23) As can be seen from the Table 1, in both the cases the estimated coefficients are significant and their sign and dimension are consistent with previous estimates found in the literature. Moreover, our new variable, i.e. the change in futures prices, is highly significant and of the expected sign.
5.3. Discussion of the results
On a comparison of goodness fit, the additional variables seem to do a good job of explaining the serially correlated shocks considered in specification (18). This finding is consistent with the view that indicators of financial stress are among the persistent, serially correlated, omitted variables. These findings also suggest a role for futures market movements, and in particular of the stabilization of basis risk, in the monetary policy of the Fed.
In order to appreciate the relative importance of futures market movements compared to the other indicators, we can follow the analysis developed in Rotondi and Vaciago (2005), and examine the contribution in percentage terms of each explanatory variable to the target value for the interest rate. This is done in Figs. 1 and 2 for the interest rate based on specifications (22) and (23), respectively. Fig. 1 shows that the component corresponding to the credit spread is of overwhelming importance, even when is compared to the inflation component. This is implausible. When the lagged credit spread is taken into account, as in Fig. 2, a more plausible picture emerges. Here inflation plays a dominant role, even if the credit spread remains a relatively very important component. In both cases a component related to futures prices is also relatively important, approximately of the same magnitude as the output gap component, and bigger than the component related to stock market movements. As relatively little attention has been paid to futures prices movements (and the stabilization of the basis risk) in the literature on monetary policy, this finding may be surprising.
16 The estimates obtained with the lagged quarterly average of the credit spread imply a worse goodness of fit compared to the case of previous period credit spread for end-of-quarter data. Details on this estimation, not reported for brevity reason, are available upon request.
J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112 109
Fig. 1. Interest rate target decomposition (current credit spread; components ordered from the bottom).
Caution is needed, however, in the interpretation of these results. While the inclusion of these additional variables is prompted by considerations of financial stability, their empirical signifi- cance is open to alternative interpretations. Although lagged values of the variables have been used, all three, the stock market index, the yield on long bonds, and the interest rate futures
Fig. 2. Interest rate target decomposition (lagged credit spread; components ordered from the bottom).
110 J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112
variable are forward-looking variables, and reflect the expectations of market participants on the future path of interest rates, among other things. A rise in the stock market may result from market beliefs about stronger future earnings growth, which subsequently induces the Federal Reserve to raise interest rate to contain inflation. The effect of higher yields on Treasury bonds relative to commercial bonds may be there because the bond markets anticipate that interest rates are about to rise. The effect of a higher rate on interest rate futures contracts in the preceding period may reflect market anticipations of higher interest rates this period. In the absence of a complete structural model, using only a single equation, there are many possible causal connections among these variables, among which it is not possible to distinguish. Consequently the findings here have to be viewed as being suggestive only, and not conclusive.
6. Conclusions
This paper contributes to the literature in several directions. Using a theoretical argument, the paper shows how stabilizing futures market movements may lead to indeterminacy of the rational expectations equilibrium, extending an analysis of Bullard and Schaling (2002). The empirical analysis allows for a Federal Reserve reaction to futures prices in the Taylor Rule. Many variants of Taylor’s original specification have been estimated. A common finding is that the lagged interest rate enters estimated policy rules with overwhelming significance. This is generally interpreted as central banks’ smoothing of interest rates to promote financial stability. More recently empirical evidence has emerged that monetary policy reacts to stock market and credit spread movements. This has also been interpreted as an attempt to promote financial stability. We add new evidence that interest rates react to futures market movements and provide a broad assessment of the relative importance of alternative indicators of financial markets stress. Our results show that the component in the interest rate rule related to futures prices has the same degree of importance of the output gap component, while it appears to dominate the stock market component. However, the empirical evidence advanced in the paper needs to be read with some caution. The results are based on single equation model not a structural model. The variables with which the interest rate rule has been augmented are all expectational variables, and may merely show up the financial markets’ anticipations of events, which later on cause changes in the Federal Reserve’s policy rule. More work is needed to distinguish among the several possible causal connections among these variables.
In both the theoretical and empirical analyses we argue that the futures market, and in particular the basis risk implied by the hedging strategies of financial institutions, is a key component of monetary policy aimed at achieving financial stability among other objectives. Surprisingly, the literature on monetary policy and financial stability has devoted little attention to the role played by futures markets, focusing mainly on the issue of stabilizing short-term interest rate fluctuations or reacting to other indicators of financial markets stress. From this perspective our paper may represent an effort towards a broader comprehension of the nexus between monetary policy and financial stability.
A graphical decomposition of the interest rate targets shows that, starting from the late 1980s, variables related to macroeconomic stability have decreased in prominence, whilst the financial stability variables have gradually come to the fore. This may have gone hand in hand with a shift in the central bank’s objective function towards financial stability motives, due to both a low inflation environment and the globalization of financial markets. If monetary policy should pay greater attention to the build-up of financial imbalances in a globalized world, the symptoms of financial instability should even be more relevant under moderate inflation dynamics. In fact,
J. Driffill et al. / Journal of Financial Stability 2 (2006) 95–112 111
during prolonged periods of price stability, build-up of debt and overinvestment by firms are more likely to occur, as under this circumstance it is more likely that excess demand pressures show up first in credit aggregates and asset prices, rather than in real market prices. The central bank’s objective function in a globalized world clearly deserves further investigation, since better under- standing of it could help in the formulation of arrangements and policy responses to promote both monetary and financial stability. As shown by the present empirical analysis, the standard textbook treatment of central bank’s objective function, mostly based on price and output stabilization, may be a too restrictive description of central banking in practice.
Acknowledgements
We are grateful to Glenn Rudebusch for having kindly provided part of the data used in the present analysis. We thank Paul Wachtel, Robert Eisenbeis and other participants at the conference “Derivatives and Financial Stability” (Rome, University “Luiss-Guido Carli”, October 25, 2005) for helpful comments. We also thank Chiara Oldani, Giovanna Paladino, Giacomo Vaciago for useful discussions on the subject, and Alessandra Balbo for excellent research assistance. Any opinions expressed are those of the authors and do not involve the institutions they are affiliated with.
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Rotondi, Z., Vaciago, G., 2005. The Fed’s reaction to asset prices. Rivista di Politica Economica 3–4, 221–243. Rudebusch, G., 2002. Term structure evidence on interest rate smoothing and monetary policy inertia. J. Monet. Pol. 49,
1161–1187. Sack, B., 2004. Extracting the expected path of monetary policy from futures rates. J. Futures Markets 24, 733–755. Sack, B., Rigobon, R., 2003. Measuring the reaction of monetary policy to the stock market. Quart. J. Econ. 118, 639–669. Schinasi, G.J., 2003. Responsibility of central banks for stability in financial markets. International Monetary Fund,
Working Paper 03/21, Washington, US. Smith, R.T., van Egteren, H., 2004. Interest Rate Smoothing and Financial Stability. Working paper, University of Alberta,
July, Edmonton, Canada. Tobin, J., 1969. A General equilibrium approach to monetary theory. J. Money, Credit, Banking 1, 15–29. Walsh, C.E., 2003. Monetary theory and policy. MIT Press, Cambridge, MA. Woodford, M., 2003. Interest and Prices: Foundations of a Theory of Monetary Policy. Princeton University Press,
Princeton and Oxford.
- Monetary policy and financial stability: What role for the futures market?
- Introduction
- Definitions of financial stability
- The importance of the futures market for financial stability: the case of financial institutions
- Monetary policy and futures market movements
- The model
- Determinacy of equilibrium
- Main findings
- Measuring the response to futures prices
- Baseline interest rate rule
- Augmented interest rate rule
- Discussion of the results
- Conclusions
- Acknowledgements
- References
Monetary-policy-bank-leverage-and-financial-stability_2014_Journal-of-Economic-Dynamics-and-Control.pdf
Contents lists available at ScienceDirect
Journal of Economic Dynamics & Control
Journal of Economic Dynamics & Control 47 (2014) 20–38
http://d 0165-18
E-m
journal homepage: www.elsevier.com/locate/jedc
Monetary policy, bank leverage, and financial stability
Fabián Valencia International Monetary Fund, 700th 19St. NW., Washington, DC 20431, United States
a r t i c l e i n f o
Article history: Received 16 June 2012 Received in revised form 2 September 2013 Accepted 11 April 2014 Available online 23 July 2014
JEL classification: C61 E32 E44
Keywords: Financial stability Bank leverage Risk-taking Monetary policy Macroprudential regulation
x.doi.org/10.1016/j.jedc.2014.07.010 89/& 2014 International Monetary Fund. Pu
ail address: [email protected]
a b s t r a c t
This paper shows that with limited liability banks lever up excessively to finance new loans. Lower monetary policy rates can worsen or reduce these incentives depending on the size of the shock when equity financing is ruled out. When this constrained is relaxed but the bank faces costly dividend adjustment, lower monetary policy rates always worsen risk-taking incentives and the effect is persistent. The reason is that costly dividend adjustment lowers the opportunity cost of lending. In this model, capital requirements are closer to the source of the distortion and thus work better than loan- to-value caps in reducing excessive risk taking.
& 2014 International Monetary Fund. Published by Elsevier B.V. All rights reserved.
1. Introduction
Motivated by the global financial crisis, some proponents have argued that easy monetary conditions, like the ones prevailing just before the mid 2000s in the United States, could lead to excessive bank risk-taking (e.g. Taylor, 2007; Borio and Zhu, 2008), through what has been labeled the risk-taking channel of monetary policy. The idea is that low interest rates may encourage banks to take more risk to boost profitability. Simple stylized facts, such as a negative correlation between the level of policy rates and measures of bank risk-taking, are consistent with this hypothesis (Fig. 1 and De Nicoló et al., 2010).
Since then, a number of empirical studies have explored this correlation aiming at establishing a causal relationship between low monetary policy rates and bank risk-taking (e.g. Jimenez et al., 2014; Ioannidou et al., 2009; Altunbas et al., 2010; Dell'Ariccia et al., 2013). And the highly expansionary monetary stance in the United States following the crisis has further fueled the interest in this issue (Rajan, 2010 and others). Shedding light on this question is important because it highlights possible unintended consequences of monetary policy on financial stability.
Consistent with the above empirical evidence, this paper rationalizes a link between monetary policy and banks' risk- taking incentives in a dynamic bank model, and studies the conditions under which risk-taking can be excessive. It exploits a well-established result in the banking literature, which is that limited liability induces banks to take excessive risk (e.g. Hellmann et al., 2000; Rochet, 2009) but innovates in showing how the monetary policy stance can influence these incentives.
blished by Elsevier B.V. All rights reserved.
2.4
2.6
2.8
3
3.2
3.4
A ve
ra ge
In te
rn al
R at
in g
(+ h
ig he
r ris
k)
-2 0 2 4
Real Federal Funds Rate
Fig. 1. Internal bank risk ratings of loans and monetary policy rates. Note: Average bank ex-ante risk ratings of business loans, with higher values indicating higher risk. Source: Survey of terms of business lending, Federal Reserve Board of Governors.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 21
In the paper, changes in monetary policy rates are for simplicity modeled as an exogenous shift in the real risk-free rate. A lower risk-free rate implies a lower opportunity cost for depositors (or bank creditors) which in turn reduces marginal funding costs for the bank. These lower costs imply that it is more profitable for the bank to increase lending and thus leverage, more so in the presence of limited liability because losses are bounded.
In a simple, static version of the problem where bank capital is exogenous, the relationship between the policy rate and bank risk of default is monotonic. The bank's risk of default increases as the policy rate decreases, more so in the case of a competitive bank than in the case of a monopolistic bank. This follows from the fact that additional profits of a monopolistic bank mitigate the increase in risk of default from higher leverage. In the dynamic version of the model, these optimal leverage decisions are contrasted with what would arise under a benchmark model in which the bank internalizes the losses faced by creditors when it goes bankrupt, interpreted as a constrained social planner, to judge whether risk-taking is excessive.
In the complete model, with endogenous bank capital and dynamics, lower monetary policy rates can lead to excessive risk-taking, but the relationship can be non-monotonic. Two important cases are considered. One in which the bank cannot issue equity, and the second one in which it can but it is costly to do so. In the first case, whether low rates induce excessive risk-taking depends on the size of the shock. When the reduction in the policy rate is small enough, risk-taking may decrease because the bank's desired increase in lending can be funded with a reduction in dividends without raising leverage. But when the reduction in the policy rate is large enough, the bank can fund the desired increase in lending only through liabilities, implying higher leverage and risk of default. With limited liability, the lower the rate, the more profitable the lending becomes, and the more attractive it is for the bank to increase leverage since the bank pays its creditors only if it stays solvent.
In the version of the model with costly equity financing, leverage unambiguously rises for any reduction in the risk-free rate because dividends are adjusted gradually. Costly equity issuance is modeled by introducing a motive to smooth dividends which follows from assuming that shareholders are risk averse. This mechanism also amplifies and propagates the increase in bank's default risk because there is an implicit cost in adjusting dividends drastically, which effectively reduces the opportunity cost of lending. Allowing depositors to be risk averse as well reduces the quantitative importance of excessive risk-taking but it does not eliminate it.
Policy can improve outcomes because risk-taking can be socially inefficient. To this end, policymakers can use regulation, including capital requirements and loan-to-value (LTV) caps. In this model, capital requirements work better because they mitigate the effects of limited liability, which is the key ingredient that distorts bank incentives. By limiting bank lending, loan-to-value caps make it optimal for the bank to hold less capital and for some calibrations they may even worsen excessive risk-taking.
In terms of related literature, empirical work with microdata has provided strong evidence supporting a negative relationship between monetary policy rates and bank risk-taking. However, theoretical contributions rationalizing these empirical results and showing the conditions under which risk-taking can be excessive is still scarce. One closely related study is Dell'Ariccia et al. (2014), which arrives to qualitatively similar conclusions than those described above. However, important differences are worth noting. First, the modeling of the information problem differs, with the cited paper focusing on adverse selection issues whereas here I focus on costly state verification. The fact that conclusions are similar implies that they are robust to the modeling choice of the information problem. Second, the model in this paper is dynamic, allowing to examine how persistent excessive risk-taking can be following a monetary policy shock, whereas Dell'Ariccia et al. (2014) is a one-period model. Third, the model in this paper allows one to extract quantitative implications. The other related recent contributions include Acharya and Naqvi (2012), where the severity of the agency problem is affected by the availability of
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3822
liquidity; Diamond and Rajan (2012), where the anticipation of central bank intervention ex post to prevent runs and asset fire sales creates incentives for banks to hold illiquid assets ex ante; and Farhi and Tirole (2012), where the anticipation of monetary policy easing in response to a negative shock leads to ex-ante incentives to correlate risks.
At a broader level, the paper is also related to macroeconomic models studying the role of financial frictions on the supply side of credit in real economic fluctuations (e.g. Bernanke and Gertler, 1987; Holmstrom and Tirole, 1997; Chen, 2001; Meh and Moran, 2010; Christiano et al., 2004; Gertler and Karadi, 2010; Gertler and Kiyotaki, 2010) and to a growing literature on non-linear dynamic models with financial intermediaries and their relationship with the macroeconomy including Van Den Heuvel (2002), Brunnermeier and Sannikov (2014), Sandri and Valencia (2013), and Valencia (2014).
The next section presents the depositor–bank and borrower–bank contracts, in which I adopt the familiar Townsend (1979)'s costly state verification framework. Section 3 presents a one period version of the model to illustrate the basic channels through which the risk-free rate affects bank profitability. Section 4 presents the infinite-horizon version of the model, as well as the construction of the benchmark model. Section 5 discusses the implications of dividend smoothing. Section 6 extends the model with dividend smoothing to include risk-averse depositors. Section 7 examines the role of regulatory restrictions in the form of capital requirements and loan-to-value caps. Section 8 concludes.
2. Loan and deposit contracts
Depositors and borrowers are assumed to be negligible in size relative to the bank. Financial frictions are modeled explicitly by imposing asymmetric information between borrowers and the bank, and depositors and the bank. These information problems take the form of costly state verification in both cases, following Townsend (1979).
2.1. Bank–borrower loan contract
There is a continuum of identical, risk-neutral borrowers who live only for one period, with access to a common production technology with only capital as a variable input:
yt þ1 ¼ αt þ1Akt ð1Þ where αtþ1 is assumed to be i.i.d. mean-one, and continuously distributed over a non-negative support with its cumulative distribution function denoted by Fα, and its corresponding density f α. A denotes the contribution of other factors in production, assumed to be fixed. Capital is assumed to be funded with loans from the bank, lt, and an exogenous endowment normalized for simplicity to 1, kt ¼ lt þ1. Entrepreneurs consume any resources that remain after paying back the loan and die. There are no ex-ante information asymmetries between the bank and borrowers. They arise only after the realization of α, which is assumed to be the entrepreneurs' private information, but common to all entrepreneurs. Gale and Hellwig (1985) show that the optimal financing device in this environment is risky debt.
Profits for an entrepreneur are defined as the outcome of production minus payments to the bank, including interest and principal: αt þ1Að1þltÞ�ltRt, where Rt denotes the interest rate agreed on the debt contract. Under limited liability, an entrepreneur defaults whenever αtþ1 falls below the level at which profits are zero, denoted by αt ¼ ltRt=Að1þltÞ. In the event of default, the bank pays monitoring costs (or bankruptcy costs)1 1Zu40 to observe αtþ1, and seizes the project, as in Townsend (1979), Gale and Hellwig (1985), and Williamson (1987). The ex-post return to an entrepreneur can be summarized by2
πðαt þ1; lt; RtÞ ¼ αt þ1Að1þltÞ�ltRt if αt þ1 ZαðRt; ltÞ 0 if αt þ1 oαðRt; ltÞ
( ð2Þ
The bank is assumed to be a monopoly and makes “take-it-or-leave-it” offers to borrowers including a loan amount and an interest rate. The interest rate is such that entrepreneurs earn an expected return equal to their opportunity cost, assumed to be given by what they would obtain if they invested only the endowment in the production project. The bank has no incentives to charge a lower interest rate, but it cannot charge a higher one either because the entrepreneur can always just invest his/her endowment in the project. The interest rate, Rt, is then solved numerically from equation E½πðαt þ1; lt; RtÞ� ¼ A, which yields an interest rate schedule as a function of the amount of lending RðltÞ.
Using this function, ex-post bank revenues are given by
gðαt þ1; ltÞ ¼ RðltÞlt if αt þ1 ZαðRðltÞ; ltÞ ð1�uÞαt þ1Að1þltÞ if αt þ1 oαðRðltÞ; ltÞ
( ð3Þ
1 As in Townsend (1979) or Gale and Hellwig (1985), these verification costs can also be interpreted as bankruptcy costs, which can include legal fees, the costs of filing for bankruptcy, honoraria of appraisers, etc. One can imagine the bank incurring these costs for each loan contract that goes through bankruptcy despite the fact that all borrowers are identical.
2 For compactness, I will include as arguments of functions only those that vary over time.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 23
2.2. Bank–depositor contract
As it was the case for the entrepreneur, the bank defaults if the realization of αtþ1 falls below the level at which its capital equals zero. Denoting nt þ1 the banks' capital in period tþ1, continuity of α implies that there is a value αt such that nt þ1 ¼ 0-gðαt; ltÞ�itdt ¼ 0, where it is the deposit interest rate, dt the amount of deposits, and gð�Þ is Eq. (3). In line with the costly state verification framework, depositors pay monitoring costs 14ω4u. The latter implies that depositors are less efficient than the bank in monitoring entrepreneur's projects, justifying in this way the existence of financial intermediation.
Notice that for the bank to default, entrepreneurs must have defaulted, given that α is the only source of bankruptcy risk in the model, implying also that α
t oαt. Therefore, αt is given by
α it; dt; ltð Þ ¼ itdt
ð1�uÞAð1þltÞ ð4Þ
With the bank subject to limited liability, the payoff to a depositor is then given by
hðαt þ1; lt; dtÞ ¼ itdt if αt þ1 Zαðit; dt; ltÞ ð1�ωÞαt þ1Að1þltÞ if αt þ1 oαðit; dt; ltÞ
( ð5Þ
which follows from the assumption that deposits are one-period contracts, and that in the event of a shock negative enough to push both, banks and borrowers into bankruptcy, depositors seize the bank and liquidate entrepreneurs' projects.
Risk-neutral depositors supply funds to the bank infinitely elastically at the interest rate that leaves them indifferent between the expected return from a risky deposit and a risk-free security. Therefore, the deposit rate function, iðlt; dt; ρtÞ, solves
ρtdt ¼ itdtð1�FαðαtÞÞþð1�ωÞAð1þltÞE½αjαt þ1 oαt�FαðαtÞ ð6Þ where for compactness, from here on, I drop the arguments of α.
It is important to mention that a well-known criticism of these types of contracts is that they are not robust to stochastic monitoring (Mookherjee and Png, 1989) and are not ex-post efficient. If lenders could, they would prefer to renegotiate the contract to avoid liquidation. But this is not an option in this paper because borrowers and depositors live for only one period. However, when multi-period contracts are allowed, and liquidation is a choice variable, Krasa and Villamil (2000) show that debt is still optimal, the contract is ex-post efficient, and robust to stochastic monitoring. They also show that the costly state verification model can be seen as a reduced form of a multi-period contract with costly enforcement.
The assumption of only aggregate risk deserves some discussion. Diamond (1984) shows that depositors can delegate monitoring of projects to banks but they do not need to monitor the latter because banks can diversify the idiosyncratic component of risk in loan contracts. But this is true only if there is no aggregate risk. To the extent that there are aggregate risks, such as fluctuations in interest rates or asset prices, implying a non-zero probability of bank default even if idiosyncratic risk is diversified, no qualitative difference in results arise if I simply assume the absence of idiosyncratic risk. In this case, introducing idiosyncratic risk would only add another layer of complexity without meaningful gains.3
3. The bank's one period problem
It is useful to begin with a special case in which the bank is a static profit maximizer and takes the amount of bank capital as given, although keep in mind that bank capital will be endogeneized in the next section:
max flg
E½gðα; lÞ�idjαZα� ð7Þ
max flg
ð1�FαðαÞÞ Rl � �
þ Z α α
αð1�uÞAðlþ1Þ |fflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl{zfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl}
Expected Revenues
�idð1�FαðαÞÞ|fflfflfflfflfflfflfflfflfflffl{zfflfflfflfflfflfflfflfflfflffl} Expected Costs
ð8Þ
where for compactness, I have also dropped the arguments of i and R. Assuming that the bank holds a given amount of capital equal to q, the balance sheet constraint implies d ¼ l�q. After making this substitution into (8) I solve numerically for the optimal solution for lending as a function of the risk-free rate ρ (see appendix for parameter values).
To check whether the relationship between bank risk and monetary policy rates depends on the assumption of a monopolistic bank, the solution to the above problem is contrasted to the solution of the problem with a competitive bank.
3 This complexity arises because the default threshold for the bank would no longer be a simple analytical expression as in Eq. (4). With idiosyncratic risk, the bank's total revenues would result from averaging across realizations of idiosyncratic risk, resulting in a non-linear function of the aggregate risk, and the default threshold would have to be obtained numerically.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3824
To this end, I first obtain the optimal demand for loans from an entrepreneur, where the lending interest rate, r, needs to satisfy a given market return on loans, R, demanded by the competitive lenders:4
max flg
Aðlþ1ÞE½αjα4α�FαðαÞ�ð1�FαðαÞÞrl ð9Þ
s:t:
Rl ¼ ð1�FαðαÞÞrlþð1�μÞAð1þlÞE½αjαrα�FαðαÞ ð10Þ The optimal solution for the above problem, for a fixed amount of entrepreneurial endowment, is a demand for loans as a
function of the market return on loans, ldðRÞ. A competitive bank in turn solves for the optimal supply of loans, taking R as given, and after guaranteeing depositors an expected return equal to the risk-free rate:
max flg
Rl�ð1�μÞAðlþ1ÞE½αjαrα��ð1�FαðαÞÞiðl�qÞ ð11Þ
s:t:
ρd ¼ idð1�FαðαÞÞþð1�ωÞAð1þlÞE½αjαrα�FαðαÞ ð12Þ The above problem, for a given amount of bank capital, q, yields an optimal supply of loans as a function of the market
return, lsðRÞ. Imposing loan market clearing, lsðRÞ ¼ ldðRÞ, I find the equilibrium R, which can be used to obtain the equilibrium levels of lending, default risk of a bank and of a borrower, all as a function of the exogenously given monetary policy rate, ρ.5
Fig. 2 shows the optimal values of lending, borrowers' risk of default, FαðαÞ, and the bank's risk of default, FαðαÞ, as a function of the risk-free rate for both problems, the monopolistic (solid line) and competitive banks (dashed line). For a given level of lending, a lower risk-free rate lowers the funding costs for the bank because of a lower return demanded by depositors. The bank then finds it optimal to increase lending because marginal revenues now exceed marginal costs. As lending increases, the leverage and the risk of bank default rise, increasing the cost (and marginal cost) of lending. But these costs increase by less under limited liability than in the absence of it, boosting the bank's incentives to increase lending and leverage. This is the case because in the absence of limited liability, expected marginal costs for both types of banks are given by i0dþi whereas with limited liability they are given by i0dþi�FαðαÞði0dþiÞ�idf αðαÞ∂α=dl, with FαðαÞði0dþiÞ40 and idf αðαÞ∂α=dl40.
The above effect is qualitatively the same for the monopolistic and competitive bank. As a result, the figure shows increasing lending and risk of bank default as the risk-free rate goes down. However, the effect is quantitatively more important for the competitive bank than for the monopolistic one. This is the case because the latter extracts all the surplus from borrowers which increases when rates are low because their opportunity cost is fixed. These additional profits imply a lower increase in the risk of bank default for the monopolistic bank, however, this happens at the expense of higher risk of default for borrowers.
In essence, the above solutions generate only quantitative different effects between a monopolistic and a competitive bank. Bank risk-taking increases with low monetary policy rates for both types of markets.
4. The infinite horizon case
4.1. Modeling the bank as a firm
While the banking literature offers numerous static and short-horizon bank models, it is largely scarce in dynamic, quantitative ones. A few existing models include Peura and Keppo (2006), Van Den Heuvel (2002), and Valencia (2014).6 The mechanisms illustrated in the static example will remain operational, but having established that there are no qualitative differences between the monopolistic and competitive banks, I proceed with the monopolistic case because it is simpler to solve. Moreover, it is more natural to think of banks as having some monopolistic power over their borrowers, and given the results shown in the last section, it may be a more conservative approach for deriving quantitative implications. The loan and the deposit contract remain intact, but I introduce a few modifications to the bank's problem. First, bank capital is now endogenous; second, the bank's objective is now to maximize the present discounted value of dividends; and third, the bank cannot issue equity. Gale and Hellwig (1985) showed that in such an environment, the optimal financing device is risky debt. Thus, the assumption of no equity financing is a simplification to capture the fact that in this environment it is not optimal to issue equity because of the non-observability of α.
4 In the absence of heterogeneity we can simply write the problem in terms of the representative entrepreneur and lender. Notice however that even with idiosyncratic risk, aggregation is still trivial because of the assumption of a linear technology.
5 In Eq. (11), I have used Eq. (10) to substitute out the expected revenues of the bank conditional on no borrower default (i.e. ð1�FαðαÞÞrl). This results in the term ð1�μÞAðlþ1ÞE½α=αrα� being subtracted from Rl. Intuitively, the subtracted term represents the part of Rl that goes to depositors if their bank defaults.
6 In the cited examples, the friction that makes bank capital matter is exogenously assumed, in the form of regulatory constraints or wedges in bank funding costs. In contrast, in this paper the friction is explicitly modeled in the form of costly monitoring.
1.01 1.02 1.03 1.04
6
7
8
9
10
11
12
l
1.01 1.02 1.03 1.04
0.001
0.002
0.003
0.004
1.01 1.02 1.03 1.04
0.02
0.04
0.06
0.08
0.10
0.12
0.14
ρ
ρ
ρ
Fα
Fα
Fig. 2. Optimal lending and default risk: the one period case. (a) Optimal Lending, (b) Bank Default Risk and (c) Borrower Default Risk. Note: Optimal solutions for a monopolistic bank (solid line) and a competitive bank (dashed line).
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 25
The bank starts period t with capital nt. It observes ρt and chooses the amount of deposits, dt, lending, lt, and dividends ct. After making decisions, αtþ1 is realized, where the tþ1 subscript is used to highlight the fact that it is unknown when decisions are made. If αt þ1 Zαt, the bank collects loans and pays off depositors the agreed amount iðlt; dt; ρtÞdt. It then arrives to the next period with capital nt þ1, given by the difference between its total revenues and its liability payments. If α
t oαt þ1 oαt, borrowers default and the bank liquidates their projects. If αt þ1 rαt borrowers and the bank default and
depositors seize the bank. The banks' problem is summarized by
max fdt;ct;ltg
ð1�Fðα t ÞÞEt ∑
t ¼ 1
t ¼ s βs�tt ctjαt þ1 Zαt
� � ð13Þ
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3826
lt rdt þnt �ct|fflfflffl{zfflfflffl} qt
ð14Þ
ρt þ1 ¼ a0 þa1ðρt �a0Þþϵt þ1 ð15Þ
ct Z0 ð16Þ
nt þ1 ¼ RðltÞlt �iðlt; dt; ρtÞdt if αt þ1 Zαt ð1�μÞAð1þltÞαt þ1 �iðlt; dt; ρtÞdt if αt 4αt þ1 4αt 0 if αt þ1 rαt
8>< >: ð17Þ
where βt denotes the discount factor, assumed to be βt ¼ 1=ðρtτÞ with τ41 to rule out indeterminacy.7 Eq. (13) reflects the objective of maximizing the present discounted value of expected dividends, conditional on the bank not having defaulted. Eq. (14) tells us that the bank's liabilities and capital are at least as large as its assets, with q denoting the stock of capital net of dividends. Eq. (14) will always hold with equality because the bank has no incentives to raise more deposits than what it needs to finance its chosen amount of lending. This equation can also be interpreted as the balance sheet constraint for the bank. Eq. (15) denotes the law of motion for the real risk-free rate, which by assumption follows a mean-reverting process, where ϵtþ1 is a mean-zero, i.i.d., random disturbance. Eq. (16) is the no-equity-financing restriction. Finally, Eq. (17) corresponds to the law of motion of bank capital under limited liability.
Bellman's equation for the problem, after using (14) to substitute out deposits, is given by
Vðnt; ρtÞ ¼ maxfct;ltg ct þβtð1�FðαtÞÞEt½Vðnt þ1; ρt þ1Þjαt þ1 Zαt� n o
ð18Þ
ρt þ1 ¼ a0 þa1ðρt �a0Þþϵt þ1 ð19Þ
ct Z0 ð20Þ
nt þ1 ¼ RðltÞlt �iðlt; lt �qt; ρtÞðlt �qtÞ if αt þ1 Zαt ð1�μÞAð1þltÞαt þ1 �iðlt; lt �qt; ρtÞðlt �qtÞ if αt 4αt þ1 4αt 0 if αt þ1 rαt
8>< >: ð21Þ
When the bank defaults, it is assumed that its license is withdrawn, which translates into imposing that the value function at zero bank capital is zero. Taking into account the possible outcomes based on the realization of α, Bellman's equation, rewritten in terms of capital net of dividends q, is given by
Vðnt; ρtÞ ¼ maxfqt;ltg nt �qt þβtEt ð1�FαðαtÞÞV
αt þ Z αt α
t
V α
t
αt f αðαÞ
#)"( ð22Þ
subject to (14)–(17).8 The corresponding first order condition for q is given by9
1 ¼ ðit �ðlt �qtÞiqt ÞβtEt ð1�FαðαtÞÞVn αt
þ Z αt α
t
Vn α
t
αt f αðαÞ
#" ð23Þ
and the one for lending is given by
0 ¼ Et ½Rt þltRlt �it �ðlt �qtÞi l t�ð1�FαðαtÞÞVn
?αt
� �zfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl}|fflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl{if borrowers repay Expected Marginal Profits
þEt Z αt α
t
½αt þ1ð1�uÞ�it �ðlt �qtÞilt�Vnα t
αt f αðαÞ
! |fflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl{zfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl}
if borrowers default Expected Marginal Profits
ð24Þ
7 If τo ¼ 1, the bank accumulates earnings to reduce financial frictions until it self-finances entirely because i4ρ for positive leverage. This is not an interesting outcome because in reality banks are highly leveraged. With τ41, it becomes costly to self-finance entirely and while the bank would still want to accumulate earnings to reduce financial frictions, there will be a point beyond which this strategy does not pay off, generating a unique equilibrium with positive leverage. This could be rationalized by modeling the tax advantages of holding debt over equity to generate positive leverage in equilibrium. A shortcut that yields an equivalent outcome is to assume τ41. The chosen approach is simpler and it is a widely used assumption in the precautionary savings literature (e.g. Carroll, 2004).
8 For compactness I introduce the following notation: V α ¼ Vðnt þ1; ρt þ1jαt þ 1 Zαt Þ and Vα
t
αt ¼ Vðnt þ1; ρt þ1jαt 4αt þ 1 4αt Þ, and where a superscript n will
denote its derivative with respect to bank capital. 9 Derivations are shown in the appendix.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 27
where I have also dropped the arguments of it, Rt, and their derivatives, denoted by i l, iq, and Rl. Eq. (23) equates the marginal
value of dividends with the marginal value of bank capital. The marginal value of capital is composed of two terms, ðit �ðlt �qtÞiqt Þ, which corresponds to the marginal cost of raising deposits that could be saved if the bank instead increased the capital. This term represents the current-period component of the marginal value of bank capital. The second component represents the present marginal value of future dividends, since earnings retained today will generate profits in future periods.
Optimal capital, in this model, is driven by the balance of two forces: when bank capital is high its marginal value is lower than the discount factor, implying that it pays off to distribute dividends and decrease capital. On the other hand, at low levels of bank capital, the high risk of bankruptcy makes capital very valuable, more so than dividends, making it attractive to increase capital.
Eq. (24) tells us that the optimal amount of lending is such that marginal profits equal zero. The terms in the squared brackets denote the marginal profits under default and no-default of borrowers, weighted by the marginal value of bank capital in each state. The terms inside each corresponding set of brackets reflect the current period marginal profits, when borrowers default and when they do not.
4.1.1. A constrained social planner benchmark The first best in this model would be obtained by removing limited liability. However, limited liability in this model is
more general than the legal interpretation of the term. Even if shareholders's responsibilities go beyond the value of their shares by law, there will always be a limit to the losses they could effectively cover. Furthermore, they may always find mechanisms to protect their wealth, implying that an extended liability framework may not be fully enforceable. For this reason, I focus on a benchmark that can be interpreted as a constrained social planner, in which the best he can do is to force the bank to internalize the losses depositors face when the bank defaults, but everything else remains the same. Strictly speaking, this is only an approximation. In a full-fledge constrained social planner problem, agents would not internalize the impact of their actions on the return on capital A, which would be determined in equilibrium. If the aggregate production function is concave, then A would decrease with the amount of lending, which in turn would raise the risk of default because the default thresholds vary inversely with A. The social planner would internalize this effect and would choose lower bank leverage. An approximation to this problem is then to consider one in which the social planner internalizes the losses the bank imposes on creditors, which results in lower bank leverage. This problem is given by
Vðnt; ρtÞ ¼ maxfqt;ltg nt �qt þβtEt ð1�FαðαtÞÞV
αt þ Z αt 0
V 0
αt f αðαÞ
#)"( ð25Þ
with first order conditions identical to (23) and (24), except for the limits of integration in the default state, which before ranged from α
t to αt and now from 0 to αt, reflecting the fact that the planner internalizes the losses it imposes on creditors.
Fig. 3 shows the marginal value of bank capital for the baseline and benchmark models, illustrating the choice of optimal leverage for both. Essentially, I construct a version of Eq. (23) expressed in terms of the capital-to-assets ratio.10 The horizontal line corresponds to the discount factor, with the risk-free rate equal to its unconditional mean. The marginal value of bank capital is higher in the benchmark model, more so at low levels of bank capital or when the risk of default is high. In contrast, limited liability makes holding capital less valuable for the monopolistic bank because the bank does not internalize the losses it would impose on depositors if it defaulted. Consequently, the optimal capital-to-assets ratio is lower (or leverage is higher) in the baseline model than in constrained social planner benchmark.
Fig. 3. Marginal value of bank capital. Note: Marginal value of bank capital evaluated at the optimal level of lending and the unconditional mean of the risk- free rate for a range of values of q=l. Constrained social planner benchmark (solid line) and baseline model (dashed line).
10 The graph shows Eq. (23) evaluated at the optimal levels of lending, at the unconditional mean of the risk-free rate, and at different values of bank capital, as a function of the corresponding ratio of bank capital to loans.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3828
4.2. Optimal decision rules
The model is solved through backwards induction using the method of endogenous gridpoints (Carroll, 2006) until the optimal decision rules for lending and dividends satisfy a given convergence criteria. The calibration and the numerical solution method are discussed in detail in the appendix. Fig. 4 shows the converged decision rules as a function of the state variables of the problem.
The corresponding shapes are intuitive, both are increasing in bank capital. As in the one-period problem, lending increases as the risk-free rate goes down for the same reasons explained earlier. Dividends decrease when the risk-free rate goes down because the discount factor also goes down, implying a lower outside return on dividends. The kink in the dividends function corresponds to the points where the no-equity-financing constraint binds.
I obtain similar decision rules for the benchmark model and compute the difference in the banks' probability of default, FαðαtÞ, between the baseline and benchmark models evaluated at each corresponding set of optimal decision rules, for each point in the state space. Fig. 5 shows the outcome.
The figure shows that the bank takes excessive risk since the difference between default risk in the baseline and social planner models is everywhere positive, but it varies with the level of bank capital and the risk-free rate. Consider the region with high levels of capital, which is essentially the area in the state space where the no-equity financing constraint does not bind. The effect of a reduction in the risk-free rate on leverage through the increase in lending is more than offset by the reduction in dividends that follows from a decrease in the discount factor (see Fig. 4). This
Fig. 4. Lending and dividends optimal decision rules. Note: Optimal decision rules as a function of state variables obtained from backwards induction, using the method of endogenous gridpoints.
Fig. 5. Excessive risk of bank default. Note: Bank risk of default evaluated at the optimal decision rules in the baseline model minus the one corresponding to the social planner problem: Fαðαðlðn; ρÞ; lðn; ρÞ�n�cðn; ρÞ; ρÞÞ�Fαðαðlspðn; ρÞ; lspðn; ρÞ�n�cspðn; ρÞ; ρÞÞ.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 29
implies that leverage actually declines. However, because the social planner holds on average more capital, this decrease in leverage impacts its risk of default much less than in the baseline model, and as a result, excessive risk- taking in the baseline model declines.
At low levels of capital where the constraint on dividends binds, a reduction in the risk-free rate causes an increase in lending and leverage that cannot be offset by a reduction in dividends. Excessive risk-taking in this case increases with a reduction in monetary policy rates. However, even if the bank is in the region where the constraint on dividends does not bind, there can be a sufficiently large reduction in the risk-free rate such that the attractiveness of lending is high enough to induce the bank to reduce dividends to zero and to increase leverage and excessive risk-taking. In essence, the reduction in the risk-free rate can make instantaneous profits so attractive that the bank accepts a much higher risk of default, because there is limited liability.
4.3. Response to interest rate shocks
Using the optimal decision rules derived earlier, I now simulate the model to study its dynamic properties. The experiment involves a one time reduction in the risk-free rate, in period 4, starting from the stochastic steady state, defined in the calibration appendix. Given these initial conditions, the decision rules determine the optimal dividend and lending decisions. Together with the corresponding transition equations for the risk-free rate and the bank capital, I can compute the expected value of the state variables for the next period, integrating across possible realizations of α and ρ. These values are used to evaluate the optimal decision rules to get the amounts of dividends and lending for the next period, and so on. The process is repeated for 20 quarters. The outcome is shown in Fig. 6. The panel shows the responses to a 25 bps and 100 bps reduction in the risk-free rate. The first three charts show the percent deviations from the stochastic steady state for the baseline and social planners. To ease the comparison, in both models the deviations are computed using the social planner's steady state. The fourth chart shows the excessive risk-taking plot for the two shocks, computed as the difference between the bank's risk of default and that of the social planner.
Consider first the case of a small shock. The optimal decision rules (Fig. 4) imply that the bank increases lending and cuts dividends. The reduction in dividends more than offsets the impact of higher lending on leverage, causing the capital-to- assets ratio to increase. But because the planner holds more capital than the monopolistic bank, the risk of default decreases more for the monopolistic bank than for the planner. As a result, excessive risk-taking decreases as shown in the fourth figure. Lax monetary policy generates a persistent reduction in excessive risk in banking, and hence in financial fragility, as shown in the figure.
When the shock is large, the bank again cuts dividends and reduces lending. However, the desired increase in lending is high enough so that it cannot be offset by a reduction in dividends. But the bank still finds it optimal to increase leverage and face a higher risk of default. This is the same for both, the planner and the monopolistic bank. However, because of limited liability, the monopolistic bank increases lending more than the planner and excessive risk-taking shoots up. In the subsequent periods, excessive risk-taking declines substantially as higher revenues are collected, and gradually returns to the stochastic steady state. Notice than in both, the small and the large shock, the lending increase is higher under the monopolistic bank. Because of the assumption of a fixed entrepreneurial endowment, this naturally implies higher leverage and riskiness of loans, but the shocks have different implications for the riskiness of the bank. In the case of the larger shock, it is worth highlighting that when excessive risk-taking is high, it also means higher financial fragility since during this period, it would take a smaller negative shock–smaller than in steady state–to push the bank and borrowers into bankruptcy.
Fig. 6. Responses to an interest rate shock. Note: State variables are initialized at the corresponding stochastic steady state values. The shock hits in period 4 for one time only. Impulse responses are shown as percentage deviations from the social planner's stochastic steady state, except for the excessive risk- taking plot that shows the absolute difference between bankruptcy risk in the baseline and social planner models (in percentage points).
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3830
5. The model with dividend smoothing
In this section I explore what would happen if the no-equity-financing restriction is removed. Simply removing the constraint in the baseline model would not do the job because banks would simply replenish capital instantaneously, eliminating a role for bank capital. This would also be inconsistent with the tendency seen in the data of dividends to be sticky and unrealistic since it would imply that banks can issue equity instantaneously at no cost.
Several alternatives exist to incorporate these modifications. For instance, one could assume that recapitalization is costly and arrives with a delay, as in Peura and Keppo (2006), or one could simply impose dividends adjustment costs as in Jermann and Quadrini (2012). These options ultimately imply that adjusting bank capital is costly. An even simpler way to incorporate this feature is to assume risk-averse shareholders, which can be justified by assuming that shareholders do not hold diversified portfolios and a significant fraction of their wealth is invested in bank shares. The immediate implication of such an assumption is dividend smoothing. The gains from introducing these modifications are that now the model implications for the behavior of dividends are closer to the data, but as pointed out in Gale and Hellwig (1985), risk aversion complicates the shape of the optimal contract, and thus the optimality of the contract becomes less straightforward. To minimize departures from Gale and Hellwig (1985), I assume that any equity injection comes from existing shareholders who also manage the bank.
The objective of these risk-averse shareholders is now to maximize the present discounted value of the expected utility derived from dividends. Eq. (13) now becomes
max fdt;ct;ltg
ð1�FαðαtÞÞEt ∑ t ¼ 1
t ¼ s βs�tt uðctÞjαt þ1 Zαt
� � ð26Þ
where uð�Þ denotes the utility function, which satisfies u0ð�Þ40 and u″ð�Þo0. The problem is subject to (14), (15), and (17), but I no longer impose constraint (16). The Envelope Theorem implies the following Euler equations for the problem:11
ucðnt �qtÞ ¼ ðit �ðlt �qtÞiqt ÞβtEt ucðct þ1 αt
Þð1�FαðαtÞÞþ Z αt α
t
ucðct þ1 α
t
αt Þ # f αðαÞ
" ð27Þ
11 I have dropped the arguments of the dividends function for compactness and denote ct þ1 αt
¼ cðnt þ1; ρt þ1jαt þ 1 Zαt Þ and ct þ1 α
t
αt ¼ cðnt þ1; ρt þ1jαt Zαt þ 1 Zαt Þ.
Fig. 7. Optimal decision rules with dividend smoothing. Note: Optimal decision rules as a function of state variables obtained from backwards induction, using the method of endogenous gridpoints.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 31
0 ¼ Et ð1�FαðαtÞÞucðct þ1 αt
ÞðRt þltRlt �it �ðlt �qtÞi l tÞ
" # f αðαÞþEt
Z αt α
t
ucðct þ1 α
t
αt Þ αt þ1ð1�uÞ�it �ðlt �qtÞilt #
f αðαÞ "
ð28Þ
The left-hand side of Eq. (27) corresponds to the marginal utility of dividends. As before, the bank chooses how much to distribute in dividends as to equate this term with the marginal value of capital, the right-hand side of Eq. (27). The same intuition as in the model with risk neutrality applies. The marginal value of capital includes the current-period cost of raising deposits and the discounted expected marginal utility from future dividends. In the case of lending, Eq. (28) is identical to Eq. (24), with the marginal utility replacing the marginal value of bank capital because the Envelope Theorem implies that ucðctÞ ¼ Vnðnt; ρtÞ.
Fig. 7 shows the optimal decision rules as a function of the state variables. A noticeable difference between this figure and Fig. 4 is the absence of the kink in the dividends policy function because the no-equity-financing constraint has been removed.
I also construct a social planner benchmark in which the bank internalizes the losses imposed on its creditors when it defaults.12 Fig. 8 depicts the difference in risk of default between the model with dividend smoothing and its corresponding constrained social planner benchmark. At first glance, the figure is similar to Fig. 5, the sensitivity of excess risk to reductions in the risk-free rate is much higher at low levels of bank capital. However, the relationship is now monotonic. A reduction in risk-free rates always increases risk-taking, although the effect is much more pronounced at low levels of capital.
12 As before, the crucial change lies in the lower bound of the integrand when computing expected profits for the bank across realizations of α.
Fig. 8. Excessive risk of bank default in model with dividend smoothing. Note: Bank risk of default evaluated at the optimal decision rules from the model with dividend smoothing minus its corresponding social planner benchmark: Fαðαðlðn; ρÞ; lðn; ρÞ�n�cðn; ρÞ; ρÞÞ�Fαðαðlspðn; ρÞ; lspðn; ρÞ�n�cspðn; ρÞ; ρÞÞ.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3832
5.1. Response to interest rate shocks
As in Section 4.3, I examine the dynamic responses of the model with dividend smoothing to a reduction in the risk-free rate, contrasting them with its corresponding social planner benchmark. The results are shown in Fig. 9. There is no qualitative difference between the responses to a small or a large interest rate reduction.
Fig. 9. Responses to an interest rate shock in model with dividend smoothing. Note: State variables are initialized at the corresponding stochastic steady state values. The shock hits in period 4 for one time only. Impulse responses are shown as percentage deviations from the social planner's stochastic steady state, except for the excessive risk-taking plot that shows the absolute difference between bankruptcy risk in the baseline and social planner models (in percentage points).
In both cases, the bank cuts dividends and increases lending, although notice that the disparity with the social planner in terms of lending and capitalization is now larger than in the case of the model with risk-neutral shareholders. Notice also that excessive risk-taking starts now at a higher level than in the previous version of the model. These differences arise because the bank is willing to lend more and to take more risks because capital can be injected when needed. The capital-to- assets ratio declines because of the sharp increase in lending, resulting in risk of default rising more in the baseline than the
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 33
benchmark model. Recall that under risk neutrality, the bank adjusts dividends instantaneously and thus excessive risk- taking drops rapidly after spiking up. In this version of the model, however, it is costly to do so. A sharp increase in dividends would decrease the marginal utility of dividends too much, compressing the right-hand side of Eq. (28), for a given amount of lending. This induces the bank to lend more instead of distributing dividends, and thus excessive risk-taking becomes much more persistent than in the previous version of the model and a decrease in risk-free rate unambiguously increases excessive risk-taking.
6. Risk-averse depositors
Risk-averse depositors would demand a premium for risk higher than that demanded by a risk-neutral depositor. This would make it much more costly for the bank to take too much risk. To explore this issue, I now assume that depositors are risk averse. The bank's problem remains identical to the one described in the previous section, with the objective function determined by Eq. (26), subject to constraints (14), (15), and (17), but not constraint (16). Eq. (6) would now be written in terms of the utility the depositors obtain from a risky bank deposit. Formally, defining Uð�Þ as a CRRA utility function, the deposit interest rate now solves
UðρtdtÞ ¼ UðitdtÞð1�FαðαtÞÞþE½Uðð1�ωÞAð1þltÞαt þ1Þjαt þ1 oαt�FαðαtÞ; ð29Þ
and it tells us that now the interest rate on a deposit needs to be such that the depositor is indifferent, in expected utility terms, between a certain return on a default risk-free security and a risky bank return. If UðxÞ ¼ x the equation becomes identical to Eq. (6). The difference is shown graphically in Fig. 10.13
Fig. 10. Deposit interest rate with risk-averse and risk-neutral depositors. Note: Deposit rate, expressed as a factor, as a function of bank leverage in the borrower default state, defined as dt=ð1�μÞAð1þltÞ, with depositors' coefficient of relative risk aversion equal to 2.
The solutions are obtained in the same way as in the previous sections. Fig. 11 shows the excessive risk of default by the bank with risk-averse depositors for two values of the coefficient of relative risk aversion for depositors, ϕ.
The sole presence of risk-averse depositors does not eliminate excessive risk-taking. The bank still takes too much risk when the risk-free rate is lowered. Notice, however, that quantitatively the effect is less pronounced as before. Take for instance the point where bank capital equals 1. When ϕ¼2 and when the interest rate is 3.9%, excessive risk-taking is about 0.4%, when it is 2.9%, it is about 0.6% and, finally, when the risk-free rate is 1.8%, excessive risk-taking is about 0.9%. In contrast, for the model without risk-averse depositors, the corresponding values are approximately 0.5%, 0.9%, and 1.3%. With risk-averse depositors, it becomes much more expensive for the bank to maintain a high leverage, to which the bank responds by increasing bank capital, resulting also in a larger distance from the limited liability constraint and thus reducing excessive risk-taking. However, even when ϕ ¼ 8, which vastly exceeds the typical values of around 2 found in the literature, excessive risk-taking is not eliminated.
There are many more modifications to the model one can explore. However, the emergence of excessive risk-taking will persist as long as limited liability is present. Enriching the environment by lengthening the horizon for borrowers or depositors and complicating their optimization problems by introducing non-linearities in their corresponding settings are changes that would affect the monopolistic bank's decisions, but also those of the social planner. However, the difference between the decentralized bank and the social planner will still be that the former does not internalize the losses it imposes on depositors while the planner does. Even more generally, one can introduce asset prices or non-linear returns in the aggregate where the bank does not internalize the impact of its actions on these aggregate variables and their effect on the risk of default, as it was briefly explained in the constrained social planner section. This, however, would not alter the conclusions.
13 Eq. (29) can be expressed as a function of the leverage of the bank under the borrowers' default state, defined as dt=ð1�μÞAð1þltÞ.
1.018
1.029
1.039
0 1 2 3 4 Bank Capital
0.2
0.4
0.6
0.8
1.0
1.2
2
1.018
1.029
1.039
0 1 2 3 4
0.2
0.4
0.6
0.8
1.0
1.2
8
Fig. 11. Excessive risk of bank default in model with dividend smoothing and risk-averse depositors. Note: Bank risk of default evaluated at the optimal decision rules from the model with dividend smoothing minus its corresponding social planner benchmark: Fαðαðlðn; ρÞ; lðn; ρÞ�n�cðn; ρÞ; ρÞÞ� Fαðαðlspðn; ρÞ; lspðn; ρÞ�n�cspðn; ρÞ; ρÞÞ. ϕ¼coefficient of relative risk aversion of depositors.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3834
Changes to the bank model by introducing other assets or liabilities can introduce new forms of risk-taking, for instance, by lending to riskier borrowers or by taking excessive liquidity risk. This is an interesting direction for future research. The purpose of this paper, however, is first to emphasize the behavior, and for simplicity I have used only one form of excessive risk-taking, through leverage. Naturally, the next step will be to explore different manifestations of this behavior and how they interact with each other. This would matter for the design of appropriate regulatory responses.
7. Policy experiments
In this section I examine how capital requirements and loan-to-value caps can mitigate excessive risk-taking. I assume that when the capital-to-assets ratio, measured as q=l, decreases below some regulatory minimum requirement λ, shareholders are forced to inject capital to cover the shortfall. However, they can only do so ex ante, not when the bank has gone bankrupt. This assumption serves the purpose of ruling out the ability of the bank to always replenish capital, in which case depositors would never face a loss. The problem is identical to the one in Section 5, with the addition of the following constraint:
ct ¼ cnt if qt Zλlt qt �λlt if qt oλlt
( ð30Þ
where cnt denotes the unconstrained solution for dividends, whereas qt �λlt reflects the capital shortfall the bank needs to inject to meet capital requirements. A loan-to-value cap, Θ, constrains borrower's leverage and can be written as14
lt r Θ
1�Θ ð31Þ
Constraints (30) and (31) are imposed one at a time. Optimal decision rules for the bank are obtained as before, which for brevity are omitted here but are of similar shape as those in Fig. 7. When solving these versions of the model, I compute the unconditional means of the capital-to-asset and loan-to-value ratios that arise under the social planner's version of the model with dividend smoothing. Then λ and Θ are set equal to those values, which correspond to about 15% and 89%, respectively. Fig. 12 shows the excessive risk of default, computed as before, as a function of bank capital for each model, including the one without regulatory constraints. To simplify exposition, the plot shows the level of excessive risk-taking, averaging across possible realizations of the risk-free rate.
Capital requirements reduce excessive risk-taking, but its effect is more visible at low levels of capital. In fact, when capital is high, and capital requirements are tighter (raised to 17%) risk-taking may be inefficiently low (excessive risk-taking is negative). However, in this model, LTV caps do little, or may even worsen risk-taking at low levels of capital, and are much more distortionary than capital requirements at high bank capital levels (excessive risk-taking is much more negative). Tighter LTV's accentuate these effects. The reason behind these results is that LTV caps constrain the leverage of borrowers but not that of the bank. As a result, they may bind at levels of bank capital where one does not want them to bind because the bank has enough capital to withstand losses if they arise. And they are lax precisely in the region where one wishes that they were binding, when the bank has little capital and the incentives to take excessive risk are strong. Since in the model bank capital is endogenous, the bank anticipates the possibility of LTV caps binding and thus not being able to lend as much as it wants and thus it decides to hold less capital. This explains why excessive risk-taking may worsen for some levels of bank capital.
14 Recall that the value of borrowers' assets is given by lt þ1 where equity equals 1. The loan-to-value ratio is given by ΘZlt=ðlt þ1Þ.
No constraints
0.91
0.89
15
17
1 2 3 4 Bank Capital
0.5
0.0
0.5
1.0
Fig. 12. Excessive risk of bank default under regulatory requirements. Note: Bank risk of default evaluated at the optimal decision rules from each version of the model minus the one corresponding to the social planner, averaging across possible realizations of the risk-free rate.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 35
In Fig. 13, excessive risk-taking is now shown as a function of the risk-free rate, averaging across possible realizations of bank capital, computed using simulated data.15 Excessive risk-taking is uniformly lower in the model with capital requirements than the model with no constraints, and again it shows that capital requirements perform better than LTV caps in this model.
No constraints
0.89
0.91 15
17
1.020 1.025 1.030 1.035 Risk free Rate
0.0
0.2
0.4
0.6
0.8
1.0
Fig. 13. Excessive risk of bank default under regulatory requirements. Note: Bank risk of default evaluated at the optimal decision rules from each version of the model minus the one corresponding to the social planner, averaging across possible realizations of the risk-free rate.
This analysis should not be interpreted as the last word on the relative effectiveness of these two regulatory tools, mainly because they have not been chosen optimally. However, it serves the purpose of highlighting two conclusions: (1) both would be more effective if they were contingent on aggregate conditions since excessive risk-taking varies with the risk-free rate, and (2) regulatory tools that are more targeted or that are closer to the source of the distortion work better. In this case, capital requirements work better because the source of the distortion is limited liability.
8. Conclusions
This paper developed a dynamic bank model to understand what may lead banks to take more risks when monetary policy rates are low and the conditions under which it can be excessive. In the model, a decrease in the risk free rate, for a given return on entrepreneurs' projects, makes lending more profitable, and this profitability is boosted by limited liability because the higher funding cost associated with higher bank leverage is only partially internalized by the bank. This mechanism is present in a monopolistic or a competitive bank, but it can be highly non-linear. When banks cannot issue equity, the effect depends on the size of the shock with small reductions in the monetary policy rate possibly reducing excessive bank risk-taking and large reductions in the policy rate increasing it. When the no-equity-financing constrained is relaxed, lowering monetary policy rates unambiguously increase excessive risk-taking and the effect tends to be more persistent.
15 To this end, I simulate 300 paths of 1000 periods each and compute the empirical distribution of bank capital from these simulated data, and these probabilities are used to average excessive risk-taking across possible values of bank capital.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3836
In this model, capital requirements perform better than imposing loan-to-value caps in reducing excessive risk-taking because they are closer to the source of the distortion. Because excessive risk-taking is a function of aggregate conditions, in this case the policy rate, the model supports the use of financial regulation contingent on macroeconomic conditions.
Acknowledgement
I am grateful to Larry Ball, James Bullard (the editor), Christopher Carroll, Stijn Claessens, Manthos Delis, Giovanni Dell'Ariccia, Luc Laeven, an anonymous referee, and seminar participants at the IMF, and Finlawmetrics 2013 workshop, for comments and discussions. The views expressed herein are those of the author and should not be attributed to the IMF, its Executive Board, or its management.
Appendix A. Calibration
The parameters of the model are chosen to match the unconditional moments from simulated data to those seen in the data for the variables listed in Table A1. The unconditional means for the model are computed from simulating 300 paths, each for 1000 periods, for each model. The parameter u¼0.12 is chosen from Bernanke et al. (1999). The one for depositors, ω ¼ 0:20, is set equal to the median losses as a fraction of assets faced by the FDIC in bank resolutions (see Laeven and Valencia, 2010). The parameters of Eq. (15) are estimated from quarterly data on treasury bond yields, expressed in real terms using the GDP Deflator, from 1985 to 2010. The estimation yields the following results: a0 ¼ 1:0288, a1 ¼ 0:82, and ϵ is Nð0; σϵÞ with σϵ ¼ 0:0067. σα ¼ 0:08 and A ¼ 1:06 are chosen as to match the bank intermediation spread, the difference between lending and deposit rates, and the risk spread, the difference between deposit rates and the risk-free rate, to those seen in the data. τ ¼ 1:025 is chosen as to match the capital-to-assets ratio, defined as the ratio of capital net of dividends to loans. For the model with dividend-smoothing, I chose a utility function of the CARA type, uðxÞ ¼ �ð1=γÞeγx, which allows for negative dividends (i.e. equity financing). The coefficient of absolute risk aversion, γ, is chosen to approximate the ratio of volatility of dividends to volatility of changes in bank capital.
Table A1 Unconditional means in model and data.
Variable Baseline With dividend-smoothing Data
Capital-to-assets ratio (%) 13.09 14.19 10.3a
Intermediation spread (%) 3.18 3.53 3b
Bank risk spread (%) 0.30 0.27 0.76c
Bank bankruptcy risk (%) 2.46 2.26 2.1d
StdðcÞ=StdðΔnÞ 0.41 0.44 0.5e
a Median capital-to-assets ratio among U.S. commercial banks during 2002–2008. b Average spread between yields on 6-month financial CD's and conventional mortgage rates over 1985–2011 in the U.S. c Average spread on one-year BBB bonds issued by U.S. banks over 2002–2008. d Average market shared of failed FDIC-insured commercial banks over 1985–2010. e Median for US commercial banks over 1978Q1–2010Q2.
The above moments are used for calibration purposes. For the dynamic simulations, however, the state variables are initialized at the stochastic steady state, defined as the point where the bank expects to remain taking into account the possible future realization of shocks. Computationally, this is obtained by iterating on the law of motion for capital, setting next-period capital equal to its expected value until it converges.
Appendix B. Numerical solution
The model and all its variants presented in this paper are solved using backwards induction and the method of endogenous gridpoints developed by Carroll (2006). The solution is implemented as follows:
1.
Start with a guess VnTðn; ρÞ ¼ 1 for the marginal value function. This assumption is equivalent to assuming that at some hypothetical last period of life, the bank distributes all its capital in dividends.
2.
Construct a discrete approximation to the normally distributed interest rate shocks using a Gaussian quadrature with 7 points, and construct a vector of possible values of the risk-free rate, covering the range a0 73σϵ, collected in ρ
- .
3.
For each ρ ϵ ρ - , I find the optimal amount of lending lnT �1 and q
n
T �1 that solve the first order conditions, using the initial guess for the marginal value function.
- -
4.Construct a vector q of values of bank capital net of dividends q. For each q ϵq , if qZqn, then the optimal solution for
dividends is cnT �1 ¼ q�qnT �1, and for lending l ¼ l n
T �1. If qoqn, the constraint on dividends binds and cnT �1 ¼ 0. In this case, I solve for lending using a root-finding procedure on the first order condition, and the beginning-of-period bank capital is given by nT �1 ¼ q.
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–38 37
5.
The solutions yield two sets of triples fρT �1; nT �1; cnT �1g and fρT �1; nT �1; l n
T �1g. Using piecewise linear interpolation I construct continuous functions lT �1ðn; ρÞ and cT �1ðn; ρÞ.
6.
Evaluating (23) with these optimal solutions I update the marginal value function and repeat the above procedure to obtain a new pair of policy functions lT �2ðn; ρÞ and cT �2ðn; ρÞ.
7.
If max ½JlT �2ðn; ρÞ�lT �1ðn;ρÞJ; JcT �2ðn;ρÞ�cT �1ðn; ρÞJ�o0:00001 for all n and ρ, the iteration stops and the last solutions on hand are the time-invariant optimal policy rules, if not, I repeat the above sequence until this convergence condition is satisfied.
In the case of the version with risk aversion, the above procedure is modified as follows:
1.
Begin with a guess for the dividends policy function cTðn; ρÞ ¼ n, which corresponds to the same assumption as before for distributing all available capital in dividends at the end of the bank's life.
-
2.Modify step 4 above as follows, for each q ϵ q I find the optimal amount of lending that solves the first order condition.
Then, I obtain the optimal amount of dividends using cnT �1 ¼ uc � 1 ðΔÞ, where uc � 1 ð�Þ corresponds to the inverse of the
marginal utility function and Δ corresponds to the right-hand side of Eq. (27).
3.I use the optimal amount of dividends on hand to obtain the beginning-of-period bank capital nT �1 ¼ q�cnT �1.
The remaining steps are identical to those for the baseline model.
When capital requirements or loan-to-value caps are introduced, the only modification to the above procedure is to set the optimal solution to either the unconstrained solution or to the one that satisfies the corresponding constraint.
Appendix C. Mathematical derivations
The first order condition for dividends is given by
0 ¼ �1þβEt 1�F αð Þð ÞVn α
dnt þ1 dq
þdnt þ1 dq
Z α α
Vn α
α f α αð Þ
#"
1 ¼ βEt Vn α ð1�FðαÞÞðit �ðlt �qtÞiqt Þþðit �ðlt �qtÞi
q t Þ Z α α
Vn α
α f αðαÞ
#"
1 ¼ βðit �ðlt �qtÞiqt ÞEt Vn α ð1�FðαÞÞþ
Z α α
Vn α
α f αðαÞ
#"
The first order condition for loans is given by
0 ¼ 1�F αð Þð ÞEtVn α
Rt þltRlt �it � lt �qt � �
iqt h i
� þ
�Etf α � �dα
dl V nt þ1; ρt þ1jα ¼ α
|fflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl{zfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflfflffl} ¼ 0
þEt Z α α
Vn α
α α 1�uð ÞRt �it � lt �qt
� � ilt
h i f α αð Þ
0 ¼ ð1�FðαÞÞEtVn α
Rt þltRlt �it �ðlt �qtÞi l t
h i þEt
Z α α
Vn α
α αð1�uÞ�it �ðlt �qtÞilt h i
f αðαÞ
For the model with dividend smoothing, the first order conditions are given by
0 ¼ �uc nt �qt � �
þβEt 1�F αð Þð ÞVn α
dnt þ1 dq
þdnt þ1 dq
Z α α
Vn α
α f α αð Þ
#"
ucðnt �qtÞ ¼ βEt Vn α ð1�FðαÞÞðit �ðlt �qtÞiqt Þþðit �ðlt �qtÞi
q t Þ Z α α
Vn α
α f αðαÞ
#"
ucðnt �qtÞ ¼ βðit �ðlt �qtÞiqt ÞEt Vn α ð1�FðαÞÞþ
Z α α
Vn α
α f αðαÞ
#"
F. Valencia / Journal of Economic Dynamics & Control 47 (2014) 20–3838
The Envelope Theorem implies
Vn ¼ βðit �ðlt �qtÞiqt ÞEt Vn α ð1�FðαÞÞþ
Z α α
Vn α
α f αðαÞ
#" Vn ¼ ucðnt �qtÞ
which after rolling it forward one period, we obtain the corresponding Euler equation for dividends
ucðnt �qtÞ ¼ βðit �ðlt �qtÞiqt ÞEt ucðct þ1Þð1�FðαÞÞþ Z α α
ucðct þ1Þf αðαÞ " #
and using the same Envelope theorem logic, the Euler equation for loans is similar to the risk-neutral case shown above:
0 ¼ ð1�FðαÞÞEtucðct þ1Þ Rt þltRlt �it �ðlt �qtÞi l t
h i þEt
Z α α
ucðct þ1Þ αð1�uÞ�it �ðlt �qtÞilt h i
f αðαÞ:
References
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Settlements. Bernanke, B., Gertler, M., 1987. Banking and macroeconomic equilibrium. In: Barnett, W., Singleton, K. (Eds.), New Approaches to Monetary Economics,
Cambridge University Press, New York. Bernanke, B., Gertler, M., Gilchrist, S., 1999. The financial accelerator in a quantitative business cycle framework. In: Handbook of Macroeconomics, vol. 1c,
pp. 1341–1393. Borio, C., Zhu, H., December 2008. Capital regulation, risk-taking and monetary policy: a missing link in the transmission mechanism? Working Paper 268,
Bank for International Settlements. Brunnermeier, M., Sannikov, Y., 2014. A macroeconomic model with a financial sector. Am. Econ. Rev. 104 (2), 379–421. Carroll, C., Nov. 2004. Theoretical Foundations of Buffer Stock Saving. Working Paper 10867, National Bureau of Economic Research. Carroll, C., 2006. The method of endogenous gridpoints for solving dynamic stochastic optimization problems. Econ. Lett. 91 (3), 312–320. Chen, N.-K., 2001. Bank net worth, asset prices and economic activity. J. Monet. Econ. 48 (2), 415–436. Christiano, Lawrence, R.M., Rostagno, M., 2004. The Great Depression and the Friedman–Schwartz Hypothesis. Working paper 10255, National Bureau of
Economic Research. De Nicoló, G., Dell'Ariccia, G., Laeven, L.A., Valencia, F.V., 2010. Monetary Policy and Bank Risk Taking. Staff Position Note 2010/09, International Monetary
Fund. Dell'Ariccia, G., Laeven, L., Marquez, R., 2014. Monetary policy, leverage, and bank risk-taking. J. Econ. Theory 149, 65–69. Dell'Ariccia, G., Laeven, L., Suarez, G., Junio 2013. Bank Leverage and Monetary Policy's Risk-taking Channel: Evidence from the United States. Working
Paper 13/143, International Monetary Fund. Diamond, D., 1984. Financial intermediation and delegated monitoring. Rev. Econ. Stud. 51 (3), 393–414. Diamond, D., Rajan, R., 2012. Illiquid banks, financial stability, and interest rate policy. J. Polit. Econ. 120, 552–591. Farhi, E., Tirole, J., 2012. Collective moral hazard, maturity mismatch and systemic bailouts. Am. Econ. Rev. 102, 60–93. Gale, D., Hellwig, M., 1985. Incentive-compatible debt contracts: the one-period problem. Rev. Econ. Stud. 52 (4), 647–663. Gertler, M., Karadi, P., 2010. A model of unconventional monetary policy. J. Monet. Econ. 58, 17–34. Gertler, M., Kiyotaki, N., 2010. Financial intermediation and credit policy in business cycle analysis. In: Friedman, B.M., Woodford, M. (Eds.), Handbook of
Monetary Economics, vol. 3. , Elsevier, Amsterdam, pp. 547–599. Hellmann, T.F., Murdock, K.C., Stiglitz, J.E., 2000. Liberalization, moral hazard in banking, and prudential regulation: are capital requirements enough?. Am.
Econ. Rev. 90 (August (1)), 147–165. Holmstrom, B., Tirole, J., 1997. Financial intermediation, loanable funds, and the real sector. Q. J. Econ. 112 (3), 663–691. Ioannidou, V., Ongena, S.R., Peydro, J.-L., 2009. Monetary Policy, Risk-Taking and Pricing: Evidence from a Quasi-Natural Experiment. Working Paper series,
Tilburg University. Jermann, U., Quadrini, V., 2012. Macroeconomic effects of financial shocks. Am. Econ. Rev. 102 (1), 238–271. Jimenez, G., Ongena, S., Peydro-Alcalde, J., Saurina, J., 2014. Hazardous Times for Monetary Policy: What do Twenty-three Million Bank Loans Say About the
Effects of Monetary Policy on Credit Risk-taking? Econometrica, 82 (2), 463-505. Krasa, S., Villamil, A., 2000. Optimal contracts when enforcement is a decision variable. Econometrica 68, 119–134. Laeven, L., Valencia, F., June 2010. Resolution of Banking Crises: The Good, the Bad, and the Ugly. Working Paper 10/146, International Monetary Fund. Meh, C., Moran, K., 2010. The role of bank capital in the propagation of shocks. J. Econ. Dyn. Control 34 (February), 555–576. Mookherjee, D., Png, I., 1989. Optimal auditing, insurance, and redistributions. Q. J. Econ. 102, 399–415. Peura, S., Keppo, J., 2006. Optimal bank capital with costly recapitalization. J. Bus. 79 (July (4)), 2163–2202. Rajan, R., 2010. Why We Should Exit Ultra-low Rates: A Guest Post. Technical Report, The New York Times: Freakonomics. Rochet, J.-C., 2009. Why Are There So Many Banking Crises?: The Politics and Policy of Bank Regulation. Princeton University Press, Princeton, New Jersey. Sandri, D., Valencia, F., 2013. Financial crises and recapitalizations. J. Money Credit Bank. 45 (November (s2)), 59–86. Taylor, J.B., August 2007. Housing and Monetary Policy. Working Paper 13682, NBER. Townsend, R., 1979. Optimal contracts and competitive markets with costly state verification. J. Econ. Theory 21 (2), 265–935. Valencia, F., 2014. Banks' precautionary capital and credit crunches. Macroecon. Dyn. 18. Van Den Heuvel, S., 2002. The Bank Capital Channel of Monetary Policy. University of Pennsylvania unpublished manuscript. Williamson, S., 1987. Costly monitoring, optimal contracts, and equilibrium credit rationing. Q. J. Econ. 102 (1), 135–145.
- Monetary policy, bank leverage, and financial stability
- Introduction
- Loan and deposit contracts
- Bank–borrower loan contract
- Bank–depositor contract
- The bank's one period problem
- The infinite horizon case
- Modeling the bank as a firm
- A constrained social planner benchmark
- Optimal decision rules
- Response to interest rate shocks
- The model with dividend smoothing
- Response to interest rate shocks
- Risk-averse depositors
- Policy experiments
- Conclusions
- Acknowledgement
- Calibration
- Numerical solution
- Mathematical derivations
- References
Reflections on the Conduct of Monetary and Financial Stability Policy.pdf
Reflections on the Conduct of Monetary and Financial Stability Policy Author(s): David A. Dodge Source: The Canadian Journal of Economics / Revue canadienne d'Economique, Vol. 43, No. 1 (Feb., 2010), pp. 29-40 Published by: Wiley on behalf of the Canadian Economics Association Stable URL: http://www.jstor.org/stable/40389554 . Accessed: 06/02/2015 11:00
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Reflections on the conduct of monetary and financial stability policy
David A. Dodge Bennett Jones LLP
1. Introduction
Eleven years ago, after my term as deputy minister of finance, I had the privilege of giving the Purvis lecture (see Dodge 1998). In that lecture, I provided a practi- tioner's reflection on the role of fiscal policy in Canada over the post-war period and set out some guidelines for the conduct of fiscal policy over the period to 2012. Today, I want to provide a practitioner's reflection on the role and conduct of monetary and macrofinancial policy.
Over the longer term the best macroeconomic contribution that governments - and their agencies including central banks - can make is to preserve confidence in three things:
1 . the soundness of public finance; 2. the future value of money; and 3. the stability of the financial system.
Confidence in macroeconomic and macrofinanical stability is a necessary pre- condition for firms to innovate and invest and for households to work and to save. Confidence in macro stability also allows governments to pursue microeconomic policies that facilitate innovation and promote rapid adjustment to changing cir- cumstances. Sound macroeconomic and macrofinanical policy -just like the rule of law and security of the person and property - is thus a part of the overall Canadian governance framework.
The Doug Purvis Memorial Lecture, delivered at Toronto, 30 May 2009. Email: [email protected]
Canadian Journal of Economics / Revue canadienne d'Economique, Vol. 43, No. 1 February / février 2010. Printed in Canada / Imprimé au Canada
0008-4085 / 10 / 29^0 / ° Canadian Economics Association
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30 D.A. Dodge
There is a symbiotic relationship between monetary and fiscal policy in achiev- ing longer-term macroeconomic stability and confidence. No central bank can pursue monetary and financial stability policy that maintains public confidence if governments at the same time recklessly create excessive public debt. In the end, poor fiscal policy will dominate good monetary policy. And that is why I argued eleven years ago that governments should aim to
1 . first reduce the ratio of public debt to GDP to a more sustainable level (I suggested 25% on a National Accounts Basis); and
2. operate thereafter to balance the budget over the business cycle.
A commitment to operating in this way would preserve public confidence in the stability of public finance over the long term while appropriately allowing the automatic fiscal stabilizers to work in the short term to reduce the amplitude of variations in output and employment. I argued that discretionary policy should be undertaken with extreme care. To the extent that discretionary fiscal stimulus was to be used in periods of very weak demand, I argued that it needed to be matched by a firm and specific commitment to discretionary reductions in expenditure or increase in taxes in periods of stronger demand. l
This practical approach to fiscal policy that I set out in 1998 is as applicable today as it was then. A Canadian federal deficit of 40 to 50 billion dollars in a year when the output gap is as large as it is likely to be in 2009 is certainly not inappropriate. But to preserve confidence in the future stability of public finances it is very important that Canadian governments (federal and provincial) now make commitments to reduce (eliminate) the new discretionary spending or to increase taxes in order to regain fiscal balance as quickly as possible after 20 10.2 This approach to prudent levels of public debt not only will contribute directly to the stabilization of output and employment in the short to medium term, but, most important, will bolster confidence in the future value of money and the stability of the financial system. I now turn to my reflections on monetary and financial stability policy.
The key long-term objectives of monetary and financial stability policy are to preserve confidence in the future value of money and confidence in the stability of the financial system. In Canada (as in many OECD countries) responsibility for preserving confidence in the future value of money has been assigned to the central bank. Responsibility for assuring financial stability has been divided between the Department of Finance, the Bank of Canada, and several prudential and market conduct regulatory authorities. The financial and economic turbulence of the last two years has called into question both the division of responsibilities and
1 Symmetrically, discretionary fiscal restraint in periods of excess demand needs to be accompanied by firm commitments to unwind the restraint later.
2 In light of our aging population, it is very important to enter the second half of the next decade with low levels of net public debt.
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Reflections on the conduct of monetary and financial stability policy 3 1
the policy frameworks that were in place prior to 2007. Major effort to rethink these frameworks is now under way globally and here in Canada. My objective today is to offer some limited reflections of a former practitioner on these policy frameworks. I will leave it to others to reflect on the division of responsibility between agencies.
2. Monetary policy
Let me begin with policy framework for assuring confidence in the future value of money. Confidence in the future value of money is important for three reasons. First, financial institutions and markets allocate capital most efficiently when there is a high degree of confidence in the future value of money. Longer-run price level certainty decreases the risk premium in longer term nominal financial contracts (see Crawford et al. 2009, 31). Second, certainty about the future value of money reduces the capricious redistribution of incomes that comes with un- expected inflation or deflation and thus promotes social stability (see Meh et al. 2009, 43). Third and most important, certainty about the future value of money actually serves to help stabilize economic output and employment in the short run, what Olivier Blanchard has called the 'divine coincidence' (for an exposition of this issue, see Dodge 2008b). Thus, certainty about the future value of money contributes to both the efficiency and stabilization responsibilities of the central bank.
In theory, it is possible to achieve simultaneously the twin goals of monetary policy - reasonable price stability and stabilization of output at a level consistent with economic potential. If demand can be kept growing at precisely the pace that the potential output of the economy is expanding, then the overall rate of inflation will remain roughly stable at the targeted rate. So the task of the monetary authority is, again in theory, relatively simple: keep the supply of money and credit growing at a rate that is consistent with allowing demand for goods and services to grow at the same rate as the real economy's ability to supply those goods and services. In practice, of course, this task is extremely complicated (see Dodge 2008a).
Given the inevitable uncertainties, a central bank needs a policy framework that minimizes the chances of making big errors in predicting the future course of output and inflation. The bank's policy framework must be communicated clearly, so that all actors - financial players, businesses, households, and governments - can reasonably be assured of the general direction of the actions the central bank will take to control inflation and stabilize output at levels close to potential over the medium term.
Since the end of the Second World War, central banks in OECD countries have struggled to find such an appropriate framework. Furthermore, central banks in both OECD and emerging economies continue to wrestle with this
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32 D.A. Dodge
problem in an increasingly interconnected financial and economic world. As I have traced this search for a monetary policy framework in another lecture (see Dodge 2008b), I will not recount this history today. As is well known, the monetary policy framework adopted in 1991 by Canada is that the Bank of Canada should set the policy interest rate with the objective of keeping infla- tion (as measured by the rate of increase in the CPI) at 2% over the medium term. This framework is conducted in the context of a floating Canadian dollar.
This inflation targeting (IT) framework has the huge advantage that it an- chors expectations of inflation. Our own experience (as well as that of other IT countries) indicates that IT has been an important contributing factor to the stability of output and employment from 1991 to 2007 (see Bank of Canada 2008).
Does this framework represent the end of monetary policy history? In 2006, well before the current economic and financial turbulence, the Bank of Canada posed two questions to stimulate research on the issue:
1 . Is 2% the right target for inflation? 2. Are there advantages to moving to a price level (or price path) target?
The summary of the research work to date on these issues is contained in the excellent papers in the Bank of Canada Review, Spring 2009.
My reading of the research on the 2% target is that there is still no clear evidence that a lower inflation target would yield economic performance significantly bet- ter than that achieved with our 2% target, although there are some indications that it might do so. There do seem to be some indications that a price level or price path target (PT) would yield superior performance - especially at times when rates have hit the zero lower bound. I think the PT might well represent an improvement to our current IT framework. A major issue to be resolved however, is the period over which policy would aim to return to the agreed-on price path. There is also a potential additional benefit that could come from the government's agreeing to a price path - namely, this would provide additional incentive for fiscal pru- dence, as the government would not be able to reduce the real burden of the debt through a one-time burst of inflation.
One other key issue raised by the Bank in 2006 was whether or not the frame- work for setting the policy interest rate should include a focus on asset prices in addition to its focus on consumer price stability. I firmly believe the answer to this question is no. In setting the policy rate, the central bank must focus on consumer price stability, although a small amount 'leaning against the wind' of rapid and sustained asset price movements may be appropriate. But since this question can be adequately addressed only in the context of the overall framework policies to promote financial stability, I will now turn to these issues.
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Reflections on the conduct of monetary and financial stability policy 33
3. Policies to promote financial stability
Market participants will always be subject to bouts of excessive exuberance and deep pessimism.3 Over- and underreaction is inherent in financial markets. Mar- ket players inevitably look to the behaviour of other market players. If everyone else is betting on continuing asset price increases - and borrowing to purchase these assets - it is hard to resist doing the same thing. This is equally true for homeowners and sophisticated fund managers. For this reason, financial mar- kets will always be characterized by successive waves of exuberance (bubbles) and pessimism (crashes). Crashes are not black swans, but are rather the inevitable outcome of a previous wave of exuberance.
The stability role of the authorities is to establish and administer a policy framework that works to dampen waves of excessive exuberance and mitigate waves of excessive pessimism. As excessive exuberance has in the past shown up in rising leverage, rapid credit growth, unrealistically narrow credit spreads, and asset price inflation, the policy framework should include mechanisms which more or less automatically serve to dampen these excesses. Similarly the frame- work should include mechanisms that mitigate the liquidity squeezes, the market collapses, the blowout of credit spreads, and the credit contractions that are the result of waves of excessive pessimism.
The central bank shares the responsibility for macrofinancial stabilization with prudential and market conduct regulators and the Ministry of Finance. In its conduct of monetary policy, financial system analysis, and financial market operations, the central bank must keep financial stability concerns in mind. In both the design and operation of the prudential framework, prudential supervi- sors must take into account what is happening 'over the dyke' in markets beyond their regulatory fiat. Similarly, agencies responsible for the oversight of markets and market conduct need to have both the mandate and the capacity not only to ensure that basic principles of disclosure are applied in all financial markets, but also to ensure that markets are continuous, that the 'mechanics' of markets are sound, and that markets do not exacerbate pro-cyclicality.
Market conduct regulators need to cooperate with prudential supervisors, central banks, and ministries of finance. All agencies with oversight responsi- bilities (including CMHC) must assume some of the burden for stabilizing the
3 Of course, central bankers too can be subject to bouts of optimism and pessimism. Following the events of 9/1 1 in 2001, the Federal Reserve, and to a lesser extent we at the Bank of Canada, were overly pessimistic about demand growth and overly feared deflationary pressures. Hence, in the United States policy rates were held too low from mid-2002 through 2004 to achieve the Federal Reserve's twin objectives of low inflation and high unemployment. For a cogent analysis of this issue, see chapter 1 of John Taylor's excellent little book Getting Off Track (2009). Partly because the U.S. policy rate was so low, we at the Bank of Canada were somewhat hesitant to raise our policy rate further than we did, even though in retrospect a slightly higher rate might have been warranted to achieve our inflation target over the medium term.
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34 D.A. Dodge
financial system. It should be in their legislated mandate.4 In other words, agen- cies responsible for prudential regulation of financial institutions and oversight of mortgage and financial markets must, in cooperation with the central bank, focus on macrofinancial stabilization issues.
Coordination and cooperation at the international level are as essential as they are at the national level. Just as we recognize that implementation is the responsibility of national authorities, the same principles of regulation need to be applied across global markets (see Financial Stability Forum 2009; G20 Working Group 1 2009).
Now let me turn to the principles of financial stability policy and the roles of central banks and regulators.
4. Central banks
A major way central banks influence financial stability is, of course, through the setting of the policy interest rate. Some have argued that central banks should set the policy rate with a view to stabilizing asset prices rather than (or in addition to) consumer prices. They argue that failure to do so is a major contributing factor to instability in financial markets, instability that can then lead to output instability.5
I would argue that in setting the policy rate central banks should continue to focus on consumer prices over the medium term, not directly target asset prices.6 Nevertheless, it is certainly true that in setting the policy rate, that is, the price of overnight credit, the central bank should take into account the evolution of the financial system. As this system evolves, so may the relationship (spread) between the price of overnight credit and the effective price of credit to households and businesses. The problem is that, during times of increasing asset prices, the compression of spreads is small.7 Thus, only small adjustments in the policy rate would be warranted to take into account the changing financial structure and lean against the wind of rising asset prices. When credit markets are under severe stress, as they have been since mid-2007, credit spreads do widen dramatically, and a much more significant adjustment in the policy rate is warranted to offset the wider spreads and achieve the deserved effective price of credit to businesses and households.
4 Note that even the Bank of Canada does not have a specific financial stability mandate, although the preamble of the Bank of Canada Act calls on it to 'regulate credit and currency in the best interest of the economic life of the Nation.'
5 See, for example, annual reports of the Bank for International Settlements (BIS) from 2004 to 2007. Some of the earliest arguments can be found in Borio and Lowe (2002).
6 Of course, house prices are included m the Canadian CPI, and hence the Bank of Canada does respond to rapid increases in the price of owner-occupied housing. See the Bank of Canada Monetary Policy Reports of 2005 and 2006, especially the report of October 2006, 33.
7 hor example, the spread between A-rated corporate bonds and Government of Canada bonds declined only about 60 bps between 2002 and 2004, but increased by about 250 bps between June 2007 and September 2008. See Dodge (2008b), 10-1 1.
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Reflections on the conduct of monetary and financial stability policy 35
But changes in the structure of financial markets affect much more than the price of credit. They dramatically affect credit availability and the terms and conditions on which credit is made available. The rapid global escalation in asset prices from 2002 to 2007 (especially in house prices) was certainly an indication of danger ahead and that policy instruments that directly affected the availability of credit needed to be deployed. Similarly, the collapse of asset prices after mid- 2007 indicated the need to deploy policy instruments that directly affect liquidity and the availability of credit.8
Adjustment of the policy rate can work well to simultaneously achieve both reasonable stability of consumer prices and financial markets when the financial structure is stable and markets are normally liquid. But in times of a rapidly evolving financial structure or in times of excessively exuberant or deeply pes- simistic and illiquid financial markets, the appropriate degree of financial and economic stabilization cannot be achieved exclusively through adjustment of the policy rate. In periods of rapid asset-price inflation, some modest increase of the policy rate from the level that would be judged appropriate to stabilize output and consumer prices might be warranted as spreads narrow. But I would con- tinue to argue that large asset-price movements indicate the need for other policy instruments to be brought to bear - instruments that influence the availability of credit rather than just the price of credit.
The central bank does have an important role to play in improving macrofi- nancial stability, a role that does not involve the use of the policy rate. The Bank of Canada is the lender-of-last-resort to the banking system and hence has a key responsibility to ensure that commercial banks maintain adequate liquidity. It also is the provider of macrofinancial analysis through the Financial System Re- view and interaction with prudential and market regulators, governments, and the private sector. And the current crisis has demonstrated that in some countries the central bank has become de facto the market maker of last resort for systemically important financial markets. Whether this should be the case de jure, is a matter for further debate. But ways to ensure the continuity of markets must be found. I will return to this issue in my discussion of the role of securities commissions, below.
It is abundantly clear that central banks need to devote (and are devoting) more effort to monitoring and assessing financial market developments, including market and institutional liquidity issues. Central banks are in the best position to assess and analyze macrofinancial developments and to make this analysis available to other agencies and the private sector.
The Bank of Canada has done this since 2003 through its semi-annual Fi- nancial System Review and is devoting much more effort to this since 2007. On stability issues, the Bank cooperates very closely with its Financial Institutions
8 This distinction between the policy rate instrument that affects the price of credit and instruments that affect the availability of credit is important. In this regard, it is interesting to reread the Porter and Radcliffe reports and the report of the U.S. Commission on Money & Credit from the early 1960s.
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36 D.A. Dodge
Supervisory Committee partners - the Canada Deposit Insurance corporation (CDIC), the Office of the Superintendent of Financial Institutions (OSFI) and the Department of Finance - but even closer cooperation is desirable going for- ward. And some way must be found to enhance cooperation on stability issues with CMHC and, most important, securities commissions. Here the Bank of Canada has a real leadership role to play.
Some have argued that such cooperation is not enough, and that micropruden- tial supervision should return to central banks. I do not believe this is necessary or necessarily desirable. But what is necessary is that central banks have the capacity to absorb and make use of microfinancial data from prudential regulators and that prudential regulators absorb and make use of the macrofinancial analysis provided by central banks.
Let me now turn to the role of prudential regulators.
5. Prudential regulators
What the experience of the last two years has clearly demonstrated is the need for prudential regulators to adopt a regulatory framework that requires financial institutions to set aside more general reserves or increase capital during the up- swing and allow them to draw on those reserves or capital during the downturn. At the very least, prudential regulators need to use 'through the cycle' measures of risk in setting the minimum risk weighted capital standards.
My own view is that regulators should require financial institutions to set aside additional provisions on the upswing and at the top of the credit cycle and allow these reserves to be drawn upon in times of financial stress. Some 'automatic' form of countercyclical provisioning would clearly improve the stability of the financial system in the same way that the automatic tax and expenditure stabilizers improve economic stability.
But the establishment of 'automatic' standards by regulators is not easy, as Superintendent of Financial Institutions Julie Dickson has said. And just as automaticity should not replace all accounting judgment, so automatic rules cannot do the whole job for prudential regulators. But at least some general principles should automatically apply - and need to be applied internationally to prevent regulatory arbitrage.
Much work to create appropriate standards is currently under way at the Fi- nancial Stability Board, the Bank of International Settlements, the International Monetary Fund, and the national central banks and regulatory authorities. I believe useful general principles can be applied. As the superintendent said: 'It may be that the most promising avenues to explore are higher quality tier 1 capi- tal; leverage ratios; loan-to-value ratios; through-the-cycle estimates under pillar 2; and loan loss provisioning. The first four were very important in terms of the Canadian banking system and allowed the system to withstand the stress of global market turmoil and also successfully raise private capital. They help to
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Reflections on the conduct of monetary and financial stability policy 37
make the system less pro-cyclical or more counter-cyclical' (Dickson 2009; see also G20 Working Group 1, 2009).9
These principles and others can be built into international standards (pillar 1). For example, loan-to- value ratios can be set to vary inversely with the rate of increase in the price of the asset class (e.g., residential mortgages). And I believe this can be done with appropriate flexibility. While precisely perfect automatic adjustment is not achievable, precise perfection should not become the enemy of the roughly good.
Let me re-emphasize that the build-up of excessive leverage earlier this decade was the fundamental cause of the problems we face today. Control of raw lever- age ratios for all financial institutions is key to ongoing financial stability. OSFFs 20-to-l maximum ratio in normal times has served Canada rather well. Gener- ally, leverage ratios for investment banks and banks outside North America are much higher. We need a set of international principles on acceptable levels of leverage.
To reduce the build-up of leverage in the cyclical upswing, higher minimum margins for financing securities need to be established by the market conduct regulator working in concert with the central bank. At the very least, required margins should be stable over the cycle. I believe that increases in these margins at times when asset prices are increasing rapidly would provide a powerful in- strument to dampen asset price volatility - a much more appropriate instrument than the use of the much blunter instrument of the policy rate.
The maximum loan-to-value ratio for insured mortgages, the terms and con- ditions of that insurance, and the minimum loan-to-value where insurance is required all are powerful tools in stabilizing housing prices. At best, these ra- tios and conditions should be adjusted to reduce procyclical behaviour. At the very least, these ratios and conditions should be stable over the cycle rather than being changed in a procyclical manner, as was the case earlier this decade.
Finally, let me emphasize that prudential regulators must pay much more attention to ensuring that banks have at all times adequate liquidity to meet con- ditions of extreme stress. In part this can be achieved through standardization of important securities and derivative instruments and ensuring continuous mar- kets for these instruments on back-stopped exchanges or clearing houses. But in the end, because it is expensive for banks to maintain adequate liquidity, much higher capital should be required for illiquid (or potentially illiquid) assets in their trading books than is currently the case, and symmetrically, lower capital charges for other assets. The banking system can function only if confidence and trust is maintained; liquidity is the fundamental bedrock upon which trust is built.
9 All the papers in the second half of the Bank of Canada's Financial System Review, June 2009, deal with the issue of procyclicality. Also see CGFS (2009).
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38 D.A. Dodge
6. Securities regulators
Because as much as two-thirds of 'traditional banking business' is now conducted directly through financial markets, securities regulators have had thrust upon them a need for broadened financial market focus. At the moment, they are currently neither professionally equipped nor legally mandated to carry out this broadened focus. This needs to change. Additional focus on full disclosure and appropriate documentation for complex products will improve stability as well as market efficiency.
But fundamentally, governments throughout the world and here in Canada need to expand the mandate of securities regulators. The mandate should be that of 'financial markets oversight' - oversight of all aspects of markets and financial products. These market overseers need to have the mandate to go beyond disclosure for certain products. They also need to enforce disclosure in what are currently exempt products.
What is most important is that some agency - whether the securities regulator or the central bank - be given the mandate to force standardization of the most important complex products and derivatives that are currently traded over the counter. Exchanges or clearing houses need to be established and central coun- terparties - complete with risk-proofed clearing and settlements systems - need to be created and monitored.
And, what is very important, the securities regulator needs to work closely with the prudential regulator to ensure not only that certain products (such as credit default swaps) trade in a transparent organized market, but that the issuer (such as the seller of credit default insurance) has adequate capital to support the product when markets are under stress.
None of this is easy. But it is vital. Continuous markets for these products must be built and backstopped. It would be easier if we had one securities regulator and one government responsible for creating the mandate. But we do not and that shouldn't stop us cooperating to get the mandates right. In Canada we have had an exemplary stability record on the macrofinancial and prudential regulatory side. We have had almost 20 years of successful monetary policy. We have a fiscal record unequalled in the major OECD countries. And we have had unparalleled cooperation between Finance, the Bank, and the prudential regulator. Surely we have the ability to create and oversee transparent and continuous securities markets.
7. Conclusion
I have tried to provide a brief tour d'horizon of the issues in monetary and financial policy based on my own experience. At the end of my Purvis lecture in 1998, I advanced 10 guidelines for future fiscal policy. Let me conclude, here, with 8 guidelines for monetary and financial policy in the decade ahead. These guidelines
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Reflections on the conduct of monetary and financial stability policy 39
are broad and general, reflecting my experience that in the area of monetary and financial policy it is far better to be 'general and roughly right 'than to be 'specific and precisely wrong.'
1 . The main long-run contribution a central bank can make to the welfare of citizens is to preserve confidence in the future value of money. While the Bank of Canada does need to be cognizant of changes in financial market structures in setting the policy rate, monetary policy should continue to be set to achieve consumer price stability.
2. Our general framework of inflation targeting is working reasonably well both in anchoring expectations and guiding policy to stabilize output at a level close to potential. This framework should be continued in the coming decade. Some modest improvements may be possible; in particular, price level or price path targeting should be considered in the Bank's next five- year review.
3. The Bank of Canada does have an important role to play in providing macrofinancial analysis at all times and in providing liquidity to financial institutions in times of stress. The Bank will have to devote more effort to the monitoring and analysis of systemic risks that are building in the financial system as innovation takes place, and regulators will have to become better equipped to use that analysis. The objective is not to stifle innovation but to ensure a better understanding of the systemic risks posed by innovation and devise ways to mitigate the systemic risks that will arise because ofthat innovation.
4. Prudential regulators will need to find some way to introduce counter- cyclical capital buffers or reserves for banks. At the very least, the procycli- cal bias in the current system needs to be eliminated. The basic principles applicable globally (pillar 1) should include some automatic adjustment, although such adjustment will be rough and not necessarily completely ad- equate. It will be up to national regulators to make additional judgments (pillar 2) with respect to what additional or lesser reserves (or capital) should be required.
5 . Minimum margins for financing securities transactions and minimum hair- cuts for derivatives need to be established and enforced. At the very leas, these should be stable over the cycle, although preferably counter-cyclical in their application. Loan-to-value ratios for residential mortgages and terms and conditions for mortgage insurance should also at the very least be stable over the cycle, although preferably counter-cyclical in operation.
6. Securities commissions will need a mandate to ensure that all issuers of all securities provide all purchasers with adequate information. Systemically important derivative products (including credit default swaps) need to be standardized. The securities regulator (or the central bank) will need a mandate to create (or cause to be created) and oversee continuous markets for these systemically important instruments.
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40 D.A. Dodge
7. Financial institutions themselves need to manage risks better over the course of the cycle. Continuous stress testing using 'improbable' scenarios is essential. It is important that institutions are given incentives to improve their own practices but that these incentives not be stifled by overly detailed prescriptive rules.
8 . Finally, cooperation is essential - both nationally and globally. The Bank of Canada, regulators, and the private sector need to work together at home to build a stronger system. We have cooperated well in Canada but can do even better. And we can provide leadership to promote international cooperation to forge a better framework for global macrofinancial and prudential policies.
References
Bank of Canada (2006) Renewal of Inflation Control Target: Background Information, November
Borio, G, and P. Lowe (2002) 'Asset prices, financial and monetary stability: exploring the nexus,' BIS Working Paper 1 14, July
CGFS (2009) The Role of Valuation and Leverage in Procyclicality, Publication No. 34, April
Crawford et al. (2009) 'Price-level uncertainty, price level targeting and nominal debt contracts,' Bank of Canada Review, Spring
Dickson, Julie (2009) Remarks to the Asian Bankers Summit, OSFI, 12 May. www.osfi- bsif.gc.ca - under speeches
Dodge, David A. (1998) Reflections on the role of fiscal policy, Canadian Public Policy, September, 275-89
- (2008a) Eric Hanson Memorial Lecture, University of Alberta, February. http://www.uofaweb.ualberta.ca/economics2/pdfs/04-Feb-08-David-Dodge- Hanson-Lecture.pdf
- (2008b) 'Central banking at a time of crisis and beyond,' Benefactors Lecture, CD. Howe Institute, November, www.cdhowe.org - under search publications/dodge
Financial Stability Forum (2009) Report of the FSFon Addressing Stability in the Financial System, April.
O20 Working uroup 1 (2009) Enhancing Sound Regulation and Strengthening Trans- parency, Final Report, 25 March; G20 'Declaration on Strengthening the Financial System,' London, 2 April
King, Mervyn (1995) 'Do inflation targets work?' Bank of England Quarterly Bulletin Men et al. (2009) Unexpected inflation and redistribution of wealth in Canada Bank of
Canada Review, Spring Taylor, John B. (2009) Getting Off Track: How Government Actions and Interventions
Caused, Prolonged, and Worsened the Financial Crisis (Stanford, CA: Hoover Institu- tion Press)
Walsh, Carl (2008) 'Inflation targeting: what have we learned?' Bank of Canada, July
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- Article Contents
- p. [29]
- p. 30
- p. 31
- p. 32
- p. 33
- p. 34
- p. 35
- p. 36
- p. 37
- p. 38
- p. 39
- p. 40
- Issue Table of Contents
- The Canadian Journal of Economics / Revue canadienne d'Economique, Vol. 43, No. 1 (Feb., 2010), pp. 1-403
- Front Matter
- Measuring the Gains from Trade under Monopolistic Competition [pp. 1-28]
- Reflections on the Conduct of Monetary and Financial Stability Policy [pp. 29-40]
- Structural Gravity Equations with Intensive and Extensive Margins [pp. 41-62]
- Trade Flows in a Spatial Oligopoly: Gravity Fits Well, but What Does It Explain? [pp. 63-96]
- U.S. Trade Remedy Law and Agriculture: Trade Diversion and Investigation Effects [pp. 97-126]
- Trade Diversion from Tomato Suspension Agreements [pp. 127-151]
- Does the Version of the Penn World Tables Matter? An Analysis of the Relationship between Growth and Volatility [pp. 152-179]
- Does FDI in Manufacturing Cause FDI in Business Services? Evidence from French Firm-Level Data [pp. 180-203]
- National Champions and Globalization [pp. 204-231]
- International Corporate Taxation and U.S. Multinationals' Behaviour: An Integrated Approach [pp. 232-253]
- Information Technology and Efficiency in Trucking [pp. 254-279]
- A Bioeconomic View of the Neolithic Transition to Agriculture [pp. 280-300]
- Equity-Regarding Poverty Measures: Differences in Needs and the Role of Equivalence Scales [pp. 301-322]
- The Role of Child Health and Economic Status in Educational, Health, and Labour Market Outcomes in Young Adulthood [pp. 323-346]
- The Evolution of Male-Female Earnings Differentials in Canadian Universities, 1970-2001 [pp. 347-372]
- Understanding the Wage Patterns of Canadian Less Skilled Workers: The Role of Implicit Contracts [pp. 373-403]
- Back Matter
Rough-Sets-and-the-role-of-the-monetary-policy-in-financial-stability-macroeconomic-problem-and-the-prediction-of-insolvency-in-insurance-sector-micro.pdf
European Journal of Operational Research 181 (2007) 1554–1573
www.elsevier.com/locate/ejor
Rough Sets and the role of the monetary policy in financial stability (macroeconomic problem)
and the prediction of insolvency in insurance sector (microeconomic problem)
A. Sanchis b, M.J. Segovia a,*, J.A. Gil a, A. Heras a, J.L. Vilar a
a Department of Financial Economy and Accounting I, Facultad de Ciencias Económicas y Empresariales,
Universidad Complutense de Madrid 28223, Spain b
Department of Business Economy, Universidad Carlos III de Madrid, Spain
Received 1 December 2004; accepted 1 January 2006 Available online 5 June 2006
Abstract
This paper faces two questions related with financial stability. The first one is a macroeconomic problem in which we try to further investigate the role of monetary policy in explaining banking sector fragility and, ultimately, systemic banking crisis. It analyses a large sample of countries in the period 1981–1999. We find that the degree of central bank independence is one of the key variables to explain financial crisis. However, the effects of the degree of independence are not linear. Surprisingly, either a high degree of independence or a high degree of dependence are compatible with a situation of finan- cial stability, while intermediate levels of independence are more likely associated with financial crisis. It seems that it is the uncertainty related with a non-clear allocation of monetary policy responsibilities that contributes to financial crisis episodes.
The second one is a microeconomic problem: the prediction of insolvency in insurance companies. This question has been a concern of several parties stemmed from the perceived need to protect general public and to minimize the costs associated such as the effects on state insurance guaranty funds or the responsibilities for management and auditors. We have developed a bankruptcy prediction model for Spanish non-life insurance companies and the results obtained are very encouraging in comparison with previous analysis. This model could be used as an early warning system for super- visors in charge of the soundness of these entities and/or in charge of the financial system stability.
Most methods applied in the past to tackle these two problems are techniques of statistical nature and, variables employed in these models do not usually satisfy statistical assumptions what complicates the analysis. We propose an approach to undertake these questions based on Rough Set Theory. � 2006 Elsevier B.V. All rights reserved.
Keywords: Rough Sets; Financial stability; Central bank independence; Insolvency; Insurance companies
0377-2217/$ - see front matter � 2006 Elsevier B.V. All rights reserved. doi:10.1016/j.ejor.2006.01.045
* Corresponding author. Tel.: +34 91 3942569; fax: +34 91 3942570. E-mail address: [email protected] (M.J. Segovia).
1 In his words, ‘‘the issue of financial stability was part of the central banks’ genetic code’’.
2 For a description of the role of central banks in financial stability across regimes see Borio and Lowe (2002).
A. Sanchis et al. / European Journal of Operational Research 181 (2007) 1554–1573 1555
1. Introduction
The financial system plays a crucial role in eco- nomic development as responsible for the allocation of resources over time and among different alterna- tives of investment by pricing the postposition of consumption (free risk rate) and pricing the risk (risk premium). A correct functioning of the finan- cial system allows economies to reach higher levels of real growth as well as more stable macroeco- nomic conditions. In the last 20 years at least 10 countries have experienced the simultaneous onset of banking and currency crisis, with contractions in Gross Domestic Product of between 5% and 12% in the first year of the crisis, and negative or only slightly positive growth for several years there- after (Stiglitz and Furman, 1998). Therefore, pre- serving financial stability is one of the main goals for policy makers since the beginning of the mone- tary systems.
The especial role that banks play in the financial system and their specificities as money issuers explain why a great number of financial crisis had got the banking sector as protagonist. In the 1980s and 1990s several countries, including developed economies, developing countries, and economies in transition have experienced severe banking crises. Such proliferation of large scale banking sector problems has raised widespread concern, as banking crises disrupt the flow of credit to households and enterprises, reducing investment and consumption and possibly forcing viable firms into bankruptcy. Banking crises may also jeopardize the functioning of the payments system and, by undermining confi- dence in domestic financial institutions; they may cause a decline in domestic savings and/or a large scale capital outflow. Finally, a systemic crisis may force sound banks to go to bankrupt.
Preventing the occurrence of systemic banking problems is undoubtedly a chief objective for pol- icy-makers, and understanding the mechanisms that are behind the surge in banking crises in the last dec- ades is a first step in this direction. A number of studies have analyzed various episodes of banking sector distress in an effort to draw useful policy les- sons (González-Hermosillo, 1996; Kaminsky and Reinhart, 1999).
The goal of the first study we present in this paper is to identify the factors behind banking sec- tor fragility focusing on the role of monetary policy. Our panel includes all market economies for which data were available in the period 1981–1999. The
explanatory variables capture many of the factors suggested by the theory and highlighted by empiri- cal studies.
There is no clear consensus on how monetary policy and financial stability are related. In particu- lar, it is not clear whether there are any trade-offs or synergies between them. This issue is very impor- tant, since it could help to devise arrangements and policy responses to promote both monetary and financial stability. The design of monetary pol- icy should be particularly important since the cen- tral bank has a natural role in ensuring financial stability, as argued by Padoa-Schioppa (2002)1
and Schinasi (2003), and has virtually always been involved in financial stability, directly or indirectly.2
As important as to gain some insight on the macro factors which contribute to financial stability is to know fragilities that arise at the micro level. Although a sound macro economic and institutional environment is crucial to promote financial stability, supervisors have to perform a continuous basis oversigh on the individual elements that constitute the financial system: financial companies, markets, clearing and settlements institutions, etc. in order to guarantee an appropriate level of financial stability.
Although, as it is said above, many financial cri- sis are associated with the banking sector, globaliza- tion, the emergence of conglomerates, financial innovation, and system integration makes more and more difficult to isolate one part of the financial system from another. The nature of potential insta- bility may have already taken new forms as a conse- quence of the ongoing transformation of the financial system. Such recent changes in the finan- cial system might be summarized by the breakdown in the separations between financial institutions and financial markets, between the three main categories of financial institutions (banks, insurance compa- nies, and on-bank financial institutions), and between national financial systems. These separa- tions have been replaced by an increasing integra- tion of markets with banks, and of banks with other financial institutions, and by an increasing internationalization of the financial system. There- fore, new potential sources of disturbances can be identified that are closely related to this changed
1556 A. Sanchis et al. / European Journal of Operational Research 181 (2007) 1554–1573
environment. Financial instability may result from market instability and also from other financial institutions (Padoa-Schioppa, 2002). For instance, in 2001 in Australia the collapse of a major insur- ance company led to a Royal Commission of Inquiry as contagion was spread through the small business sector via denial of insurance or claims for certain activities or incidents, or through higher premiums.
Among the components of the financial system in the second study we present in this paper we focus on the insurance sector because, although it plays a growing and crucial role in modern economies, it has received less attention from researches. More- over, given its business peculiarities it is not possible to translate the conclusions from banking sector analysis to the insurance sector and therefore a spe- cific analysis is needed.
The insurance industry is of fundamental eco- nomic and social importance. It has long been recog- nized that there needs to be some form of prudential supervision of such entities to attempt to minimize the risk of failure. Nowadays, Solvency II project is intended to lead to the reform of the existing sol- vency rules in European Union. Therefore, develop- ing new methods to tackle the problems we have mentioned above is a highly topical question.
In this paper we tried to show how the methodol- ogy we propose is flexible enough to tackle with both problems, the analysis at macro and micro level outperforming previous analysis.
In the past a large number of methods have been proposed to deal with these two matters. Most approaches applied are statistical techniques such as discriminant or logit analysis. In most cases, the attributes employed as explicative variables do not usually satisfy statistical assumptions. So in order to avoid these inconveniencies of statistical meth- ods, we propose an approach to predict insolvency of insurance companies and financial instability in a country based on Rough Set Theory (RS Theory).
Some of the advantages of this theory are: first, it is a useful tool to analyse information systems rep- resenting knowledge gained by experience; second, we can use qualitative and quantitative variables and it is not necessary that the variables employed satisfy any assumption; third, through this analysis the elimination of the redundant variables is got, so we can focus on minimal subsets of variables to evaluate insolvency or instability and, therefore the cost of the decision making process and time employed by the decision maker are reduced;
fourth, the analysis process results in a model con- sisted of a set of easily understandable decision rules so usually it is not necessary the interpretation of an expert and finally, fifth, these rules are based on the experience and they are well supported by a set of real examples so this allows the argumentation of the decisions we make.
In this paper we applied the RS analysis to get closer to the factors that can contribute to financial stability in a country. The RS analysis allows over- coming some of the rigidities of other methodolo- gies previously applied as logit and probit analysis. This paper also completes previous researches for prediction of banks bankruptcy based on RS Theory (Dimitras et al., 1999; Greco et al., 1998; Mckee, 2000; Slowinski and Zopounidis, 1995; Zopounidis and Dimitras, 1998) developing a prediction model for insurance companies. The results are very encouraging in comparison with more traditional techniques.
A financial crisis is the sum, significant enough, of several individual crises together. The time coinci- dence of these individual crises can be explained by common factors affecting the financial sector, as in any other sector, or by contagion. The peculiarity of the financial sector is that the contagion can arise through affecting consumer confidence. For instance, a sharp fall in depositor’s confidence can lead to an unexpected withdraw of deposits, which can pose problems even in otherwise sound financial companies. Moreover, there are other contagion mechanisms as the ownership links, commercial links, etc. Therefore, at the extent the crisis of a financial company can be contagious, this individual crisis could trigger a systemic crisis. Once a financial crisis is on going, the likelihood of a crisis in other financial companies also increases. This feedback mechanism is the typical feature of a financial crisis.
Although we treat in this paper both problems separately, an obvious step forward would be to develop an integrate model that accounts for the links between the crisis of an individual financial company and a systemic financial crisis. In the meantime, we think the use of the macro model to monitor the macro factors that can increase the like- lihood of a financial crisis together with the models at a micro level to monitor the probability of an individual crisis can help the competent authorities to prevent or, at least, mitigate the effects of a finan- cial crisis.
The rest of the paper is structured as follows: Sec- tions 2 and 3 introduce the theoretical models
3 Higher real interest rates are likely to hurt bank balance sheets even if they can be passed on to borrowers, as higher lending rates result in a larger fraction of non-performing loans.
4 For an in-depth discussion of the theory of bank runs, see Bhattacharya and Thakor (1994).
A. Sanchis et al. / European Journal of Operational Research 181 (2007) 1554–1573 1557
underlying the selection of explanatory variables for financial crisis and insurance insolvency, respec- tively. In Section 4 we explain the methodology. Section 5 describes the empirical models and the main results we obtained. Finally, Section 6 high- lights the main conclusions that can be outlined from the analysis.
2. The determinants of banking crises
Houben et al. (2004) define financial stability in terms of its ability to help the economic system to allocate resources, manage risks, and absorb shocks. Moreover, financial stability is considered a continuum, changeable over time and consistent with multiple combinations of its constituent ele- ments. In the same paper we can find an Appendix A that provides an overview of definitions or descriptions of financial stability by a selected group of officials, central banks and academics. We focused on banking crises, as a financial instability outcome, because monetary policy, which is the var- iable we want to focus, is more directly related to the functioning of the banking system than to the rest of the financial system.
The literature offers several definitions of bank- ing crises (Friedman and Schwartz, 1963; Bordo, 1986; Lindgreen et al., 1996; Caprio and Klingebiel, 1997; Gupta, 1996). However, none of which com- pletely solve the problem of how to summarize such description in one single quantitative indicator, or a set of them. Existing indicators, such as those men- tioned by Lindgreen et al. (1996), are not readily available for a large number of countries, or else there is the lack of comparable cross-country data to construct such indicator. The empirical literature has opted for identifying banking crises as events, expressed through a binary variable, constructed with the help of cross-country surveys (Lindgreen et al., 1996; Caprio and Klingebiel, 2003). This will be our approach as well.
Banks are financial intermediaries whose liabili- ties are mainly short-term deposits and whose assets are usually short and long-term loans to businesses and consumers. When the value of their assets falls short of the value of their liabilities, banks become insolvent. Moreover, the nature of their business results in banks are institutions heavily leveraged. Then the banks, apart from the common risks face by a company, also face some specifics risks.
The most characteristic risk faced by banks is credit risk, which is the risk that borrowers become
unable or unwilling to service their debt. The empir- ical literature has highlighted a number of economic shocks associated with the materialization of this risk: cyclical output downturns, terms of trade dete- riorations, declines in asset prices such as equity and real estate (Gorton, 1998; Caprio and Klingebiel, 1997; Lindgreen et al., 1996; Kaminsky and Rein- hart, 1999).
Another typical bank risk is the interest rate risk. Because the asset side of bank balance sheets usually consists of loans of longer maturity at fixed interest rates, the rate of return on assets cannot be adjusted quickly enough, and banks must bear losses. Thus, a large increase in short-term interest rates is likely to be a major source of systemic banking sector prob- lems. In turn, the increase in short-term interest rates may be due to various factors, such as an increase in the rate of inflation, a shift towards more restrictive monetary policy that raises real rates, an increase in international interest rates, the removal of interest rate controls due to financial liberaliza- tion (Pill and Pradhan, 1995), the need to defend the exchange rate against a speculative attack (Velasco, 1987; Kaminsky and Reinhart, 1999).3
Another risk banks face is currency risk, when banks borrow in foreign currency and lend in domestic currency. In this case, an unexpected depreciation of the domestic currency threatens bank profitability. Foreign currency debt was a source of banking problems in Mexico in 1995, in the Nordic countries in the early 1990s, and in Tur- key in 1994 (Mishkin, 1996).
Liquidity risk is one of the most characteristic risks of banks. When bank deposits are not insured, deterioration in the quality of a bank’s asset portfo- lio may trigger a run, as depositors rush to with- draw their funds before the bank declares bankruptcy. Because bank assets are typically illiq- uid, runs on deposits accelerate the onset of insol- vency. The possibility of self-fulfilling runs makes banks especially vulnerable financial institutions. A run on an individual bank should not threaten the banking system as a whole unless partially informed depositors take it as a signal that other banks are also at risk (contagion).4 In these circum- stances, bank runs turn into a banking panic.
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A sudden withdrawal of bank deposits with effects similar to those of a bank run may also take place after a period of large inflows of foreign short-term capital, as indicated by the experience of a number of Latin American, Asian, and Eastern European countries in the early 1990s.
The literature, therefore, suggests a variety of mechanisms that can bring about banking sector problems. In what follows, we attempt to use our data set to identify which of these mechanisms have played a major role in the crises of the 1980s and early 1990s.
Moreover, we want to focus on the role of mon- etary policy. The existing literature on monetary policy has concentrated on issues different than financial stability (mainly price stability but also output stabilization). The impact of the monetary policy design on financial stability is related to the very much debated question of the relation between price stability and financial stability. The economic literature is divided as to whether there are synergies or a trade-off between them (Mishkin, 1996; Cukier- man et al., 1992; Fisher, 1933). If synergies existed between the two objectives it would seem safe to argue that the same monetary policy design which helps to achieve price stability also fosters financial stability (Schwart, 1995; Padoa-Schioppa, 2002; Issing, 2003). However, if there were a trade-off, it would be much harder to establish an a priori on the impact of price stability on financial stability.
There is some empirical analysis, albeit still scarce, on the impact of financial instability, and in particular of banking crisis, on a country’s mon- etary policy. In particular, Garcı́a-Herrero (1997) and Martinez-Peria (2000) find empirical evidence that money demand is stable in the long run in countries having experienced systemic banking crisis. However, to the best of our knowledge only one study is available on the reverse causality, Garcı́a-Herrero and del Rio (2003). They apply a multivariate logit model to estimate the relation- ship between monetary policy design and finan- cial instability, controlling for other relevant variables.
Most of the empirical analyses conducted to find the determinants of financial instability (Demirgüç- Kant and Detragiache, 1997, 1998, 2000; Eichen- green and Rose, 1998; Frydl, 1999; Glick and Hutchinson, 1999; Gourinchas et al., 1999; Hardy and Pazarbasioglu, 1998; Rossi, 1999; Eichengreen and Arteta, 2000) or to analyse the role of a partic- ular variable in explaining financial instability, as
exchange rate regimes (Eichengreen, 1997, 2000; Kaminsky and Reinhart, 1999; Mendis, 1998; Domaç and Martı́nez Peria, 2000) or monetary pol- icy strategies (Garcı́a-Herrero and del Rio, 2003) are based on a classical probit or logit methodology (Eichengreen and Arteta, 2000). The main short- coming of this analysis is that the outcome is sum- marized in one single rule that averages the contribution of each significant variable to explain financial crisis. This methodology fails to capture the variety of rules that fully describe the reality. For instance one variable can only be significant in some circumstances while insignificant in others; or one variable can have a positive effect for some intervals of values and negative for others even non-monotonically, as we will see in our application to financial crisis.
3. Financial ratios as explicatives variables of the
insolvency in insurance sector
On the other hand, the other objective variable is insolvency in insurance sector. In general financial terms, insolvency can be referred as the impossibil- ity or inability of a firm to pay its debts. A prior per- iod of insolvency could be got over, for example, by means of the postponement in the payments of the debts. If the firm is unable to overcome this first per- iod, it can become bankrupt. Therefore, bankruptcy could be interpreted as the culmination of the insol- vency process. In any case, in this work we are inter- ested in looking for the minimal set of financial ratios that could anticipate possible insolvencies due to permanent financial problems.
There are several reasons that could explain why an insurance firm becomes insolvent (Bannister, 1997) but all of them are reflected in the financial statements. These statements are specifically affected in all items related to:
– Liquidity: One of the most important questions in order to assure the proper functioning of any firm is the need of having sufficient liquidity. But in the case of an insurance firm, the lack of liquidity should not arise due to ‘‘productive activity inversion’’ which implies that premiums are paid in before claims occur. If an insurance firm cannot pay the incurred claims, the clients and public in general could lose faith in that company. – Profitability: Profits guarantee the present and future viability of any firm. In order to measure
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this variable we will consider the results obtained and the cashflow. Sometimes it would be better use the second one because is less manipulated than the first one. – Solvency ‘‘in a strict sense’’: We have to take into account the risk exposure of the insurance firm (through premiums or incurred claims) and the real financial support (through technical pro- visions together with capital and reserves). Their comparison demonstrates the need of having suf- ficient shareholder’ funds and the need of com- plying correctly with the technical provisions to guarantee the financial viability of the insurance company.
Therefore, these three questions will be consid- ered in order to define the financial ratios that will be employed in our research.
Previous researchers applied to predict insurance insolvency in Spain are usually based on discrimi- nant analysis: López et al. (1994), Mora (1994), Martı́n et al. (1999) and Sanchis et al. (2003). There- fore same considerations about methodology as in the systemic crisis problem apply here.
4. The methodology: Main concepts of the Rough Set
(RS) Theory
RS Theory was firstly developed by Pawlak (1991) in the 1980s as a mathematical tool to deal with the uncertainty or vagueness inherent in a deci- sion making process. Though nowadays this theory has been extended (Greco et al., 1998, 2001), we refer to classical approach that does not order attri- bute domains as it assumes that different values of the same attribute are equally preferable and that only the predictive value of the attribute, as revealed by the data, will be factored into the model.
The extended approach handle dominance rela- tions, in addition to indiscernibility relations, incor- porating data about the ordering properties of the attributes analyzed, if these exit and are known. For example, if it were known that a financial ratio that was high was preferable to a financial ratio that was low, the firm with a high ratio could be consid- ered to be preferred over the firm with a low ratio and indeed all the values of the ratio could be con- sidered to be ordered. The resulted model is poten- tially more compact since some rules conflicts for certain cases are eliminated. Therefore, it uses addi- tional information to generate a simpler final model, but the classical approach makes a less restrictive
data assumption than does the extended approach (Mckee, 2000, p. 162).
The wisdom about traditional financial ratios has considered them as attributes with ordered domains. For example, a high value for a profitabil- ity ratio (net income to total assets) is preferable to a low value. This fact would imply the monotonicity between the condition attributes (financial ratios) and the decision attribute. Increasing monotonicity occurs when the larger the value of the financial ratio, the better the value of the decision attribute. Decreasing monotonicity occurs when the smaller the value of the financial ratio, the better the value of the decision attribute. However, this assumption could be questioned for purposes of insolvency pre- diction. Mckee and Lensberg (1999) employed genetic programming to develop a bankruptcy pre- diction model. The model found that bankruptcy probability could be predicted as a complex func- tion of three ratios and, further, it was found that whether a high value or low value in one of the three ratios could be considered as good news or bad news depended on the level of the other two ratios. There- fore, a higher ratio in the case of increasing mono- tonicity (for example, a high value for profitability ratio decreased business failure probability, except when the profitability ratio was unusually high because in that case it increased the predicted bank- ruptcy risk) was not always better and consequently, it would seem appropriate not to assume that finan- cial ratios have a dominance relation.
This reasoning can be also considered for the pre- diction of financial stability and, accordingly, this paper uses the classic RS theory based on indiscern- ibility relations for both financial problems.
Therefore, RS theory is related in some aspects to other tools that deal with uncertainty. However, RS approach is somewhat different to statistical proba- bility, which deals with random events in nature or fuzzy set theory, which deals with objects that may not belong only to one category but may belong to more than one category by differing degrees. On the contrary, RS theory deals with the uncertainty pro- duced when some objects described by the same data or knowledge (so, they are indiscernible) can be classified into different classes, that is, there is not a unique inclusion of these indiscernible objects. This fact prevents their precise assignment to a set. These differences show one of the main advantages of RS theory: an agent is not required to assign pre- cise numerical values to express imprecision of his knowledge, such as probability distributions in
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statistics or grade of membership in fuzzy set theory (Nurmi et al., 1996).
This section presents some concepts of RS The- ory following Pawlak’s reference and some remarks by Slowinski (1993) and Dimitras et al. (1999).
The philosophy of this approach is based on the assumption that with every object of the universe we are considering we can associate knowledge, data. Knowledge is regarded as ability to classify objects. Therefore knowledge consists of a family of various classification patterns of a domain of interest. Objects described by the same data or knowledge are indiscernible in view of such knowledge. The indiscernibility relation leads to mathematical basis for the RS Theory. Vague information causes indis- cernibility of objects by means of data available and, as a result, this prevents their precise assign- ment to a set. Intuitively, a rough set is a set or a subset of objects that cannot be expressed exactly by employing available knowledge. If this informa- tion or knowledge consists of a set of objects described by another set of attributes, we consider a rough set as a collection of objects that, in general, cannot be precisely characterized in terms of the val- ues of the set of attributes.
RS Theory represents knowledge about the objects as a data table, that is, an information table. Rows of which are labelled by objects (states, pro- cesses, firms, patients, candidates, . . .) and columns are labelled by attributes. Entries of the table are attribute values. Therefore, for each pair object- attribute, x � q, there is known a value called descriptor, f(x, q). The indiscernibility relation would occur if for two objects, x and y, all their descriptors in the table have the same values, that is if, and only if, f(x, q) = f(y, q).
4.1. Approximation of sets, accuracy and quality of
approximation
In general, all properties of rough sets are not absolute, but are related to what we know about them. Indiscernible objects by means of attributes prevent their precise assignment to a class. There- fore, some categories (subsets of objects) cannot be expressed exactly by employing available knowl- edge and, consequently, the idea of approximation of a set by other sets is reached. A rough set is a pair of a lower and an upper approximation of a set in terms of the classes of indiscernible objects. That is, it is a collection of objects that, in general, cannot be precisely characterized in terms of the values of
the set of attributes, while a lower and an upper approximation of the collection can be. Therefore, each rough set has boundary-line cases, that is, objects that cannot be classified certainly as mem- bers of the set or of its complement and can be rep- resented by a pair of crisp sets, called the lower and the upper approximation. The lower approximation consists of all objects that certainly belong to the set and can be certainly classified as elements of that set, employing the set of attributes in the table (the knowledge we are considering). The upper approximation contains objects that possibly belong to the set and can be possibly classified as elements of that set using the set of attributes in the table. The boundary or doubtful region is the difference between the lower and the upper approximation and is the set of elements that cannot be certainly classified to a set using the set of attributes. There- fore, the borderline region is the undecidable area of the universe, that is, none of the objects belong- ing to the boundary can be classified with certainty into a set or its complement as far as knowledge is concerned.
Inexactness of a set is due to the existence of the boundary. The greater the doubtful region of a set is, the lower the accuracy of that set. The accuracy of approximation is defined as the quotient between the cardinality of the lower approximation and the cardinality of the upper one. This ratio expresses the percentage of possible correct decisions when classifying objects employing knowledge available. Therefore, using the lower and the upper approxi- mation we can define precisely those subsets that cannot be expressed exactly using the available attributes.
Because we are interested in classifications, the quality of classification is defined as the quotient between the addition of the cardinalities of all the lower approximations of the classes in which the objects set is classified, and the cardinality of the objects set. It expresses the percentage of objects which can be correctly classified to classes employ- ing the knowledge available.
4.2. Reduction and dependency of attributes
A fundamental problem in the rough set approach is discovering dependencies between attri- butes in an information table because it enables to reduce the set of attributes removing those that are not essential (unnecessary) to characterize knowledge. This problem will be referred to as
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knowledge reduction or, in more general terms, as a feature selection problem. The main concepts related to this question are the core and the reduct. A reduct is the minimal subset of attributes which provides the same quality of classification as the set of all attributes. If the information table has more than one reduct, the intersection of all of them is called the core and is the collection of the most relevant attributes in the table.
4.3. Decision rules
An information table which contains condition and decision attributes is referred as a decision table. A decision table specifies what decisions (actions) should be undertaken when some conditions are sat- isfied. So a reduced information table may provide decision rules of the form ‘‘if conditions then decisions’’.
These rules can be deterministic when the rules describe the decisions to be made when some condi- tions are satisfied and non-deterministic when the decisions are not uniquely determined by the condi- tions so they can lead to several possible decisions if their conditions are satisfied. The number of objects that satisfy the condition part of the rule is called the strength of the rule and is a useful concept to assign objects to the strongest decision class when rules are non-deterministic.
The rules derived from a decision table do not usually need to be interpreted by an expert as they are easily understandable by the user or decision maker. The most important result in this approach is the generation of decision rules because they can be used to assign new objects to a decision class by matching the condition part of one of the deci- sion rule to the description of the object. Therefore, rules can be used for decision support.
RS Theory can analyse several multiattribute decision problems. It is especially well suited to classification problems. One of these problems is multiattribute classification problem which consists of the assignment of each object, described by values of attributes, to a predefined class or category.
We want to mention that rough set analysis has been performed using ROSE software provided by the Institute of Computing Science of Poznan Uni- versity of Technology. Any personal computer with a link to internet can access to the web http:// idss.cs.put.poznan.p1/site/rose.html where ROSE software and its manual can be downloaded. More
details about this software are given in Predki et al. (1998) and Predki and Wilk (1999).
5. Empirical results
As we have previously mentioned, RS approach is especially well suited to classification problems. One of these problems is a multiattribute classifica- tion problem which consists of the assignment of each object, described by values of attributes, to a predefined class or category. The two financial problems we are going to tackle are examples of this kind of problems. In financial instability prediction (Model 1), we try to assign countries described by a set of macroeconomic variables to a category (crisis or financial stability). In business failure prediction (Model 2), we try to assign firms (objects) described by a set of financial ratios (attributes) to a category (failed or ‘‘healthy’’ firm). In this stage of our research, we have proceeded to the election of the data and variables that will be used to develop our models.
5.1. The data
As for the data employed in Model 1, we have employed a sample of 79 countries in the period 1981–1999 (annual data). The dependent variable can be defined in this way: Systemic and non- systemic banking crises dummy equals one during episodes identified as in Caprio and Klingebiel (2003). The independent variables included are dic- tated by the theory on the determinants of banking crisis. We provide a detailed list of variables and sources in Data Appendix A. We included two types of variables in our estimations: macroeconomic variables and financial variables. Among the macro- economic variables we include: the real growth of GDP, the level of real GDP per capita, the inflation rate and the real interest rate to capture the external conditions that countries face. We have employed qualitative and quantitative variables. The possibil- ity of using both kinds of variables is one of the advantages of this methodology.
As for the data in Model 2, we have employed a sample of Spanish firms used by Sanchis et al. (2003). This data sample consists of non-life insur- ance firm data 5 years prior to failure. The firms were in operation or went bankrupt between 1983 and 1994. In each period, 72 firms (36 failed and 36 non-failed) are selected. As a control measure, a failed firm is matched with a non-failed one in
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terms of industry and size (premiums volume). In our analysis we have used data 1 year prior to fail- ure to obtain the decision rules and we have tested the rules with data from years 2, 3, 4 and 5 (Dimi- tras et al., 1999). Provided that we are looking for those financial ratios that could help the decision maker to anticipate possible insolvencies, we have to mention that our definition for insolvency (objec- tive variable) is made in strict sense, therefore insol- vent group consists of those firms that have been taken over by Spanish ministry of economy. So, the insolvent group consists of those firms that have disappeared due to permanent financial problems. This way we avoid working with firms that have temporary financial problems or that have disap- peared voluntarily. On the other hand we have checked that the firms of the solvent group have gone on working for several years after the sample period because it is possible that a firm, that has not been taken over by Spanish ministry of econ- omy can become bankrupt.
As for the variables in Model 2, we have to men- tion that each firm is described by 17 financial ratios that have come from a detailed analysis of the vari- ables, previous bankruptcy studies for insurance companies and our preferences and knowledge. These ratios (see Table A.1 in Appendix A) have been divided into four groups: A group contains ratios related to financial position; B group contains ratios related to operating account; C group con- tains ratios related to earnings and cash-flow and, finally, D group contains ratios related to provi- sions. We have to draw particular attention to the fact that special financial characteristics of insur- ance companies require general financial ratios as well as those that are specially proposed for evaluat- ing insolvency of insurance sector.
We are going to analyze results for the two mod- els separately.
5.2. Prediction of financial instability
If we developed a model and we test it with the same sample, the results obtained could be condi- tioned. So in order to avoid it, for this first model we have formed a training set, and a holdout sample to validate the obtained decision rules, i.e., the test set. Both sets have been randomly selected. The training information table consisted of 421 data from 79 countries in the period 1981–1997 (annual data) described by the variables explained in Section 4, and assigned to a decision class (crisis – 1 or not –
0). We have 293 objects for class 0 and 128 objects for class 1. The test information table consisted of 100 data described by the same variables in the per- iod 1997–1999 (36 objects for class 1, and 64 objects for class 0). So the training information table was entered into an input file in ROSE.
We have recoded the continuous variables into qualitative terms (low, medium, high and very high) with corresponding numeric values such us 1, 2, 3 and 4. This recoding has been made dividing the ori- ginal domain into subintervals. This recoding is not imposed by the RS theory but it is very useful in order to draw general conclusions from the ratios in terms of dependencies, reducts and decision rules (Dimitras et al., 1999).
The definition of the boundary values can influ- ence results of the RS analysis, in particular the quality of classification. There is not a general way to define the optimal boundary values. It is usually done by experts according to their experience, knowledge, habits or conventions, as in financial problems (Slowinski and Zopounidis, 1995; Dimi- tras et al., 1999). If there is not an expert to recode the variables that could follow their experience or standards of financial analysis, it is deemed desir- able to avoid subjective inputs to the extent possi- ble. Accordingly, the four subintervals are based on the quartiles for the actual variable values (year 1) for the whole sample because percentiles are fre- quently used in scientific researches to divide a domain into subintervals (Laitinen, 1992; Mckee, 2000). We choose this method because we have no a priori knowledge about some other partitions with more economic sense. Of course it could be justified to use fewer intervals in some variables and more in other cases, but we consider this type of discretiza- tion as a good first step in terms of the subsequent interpretation of the results. We want to mention that there are other approaches to discretize vari- ables. In fact, ROSE software has implemented an entropy-based method to get attributes with discrete domains. However, though we know that if we had employed other approaches, we would have obtained other models, this simple form of discreti- zation based on the quartiles of the distribution has provided good results in the validation tests. Never- theless, in future researches we will try other discret- ization strategies (see Table 1).
The first results obtained from RS analysis of the coded information table were: the approximation of the decision classes and their quality of classification were equal to one:
Class Number of objects
Lower approximation
Upper approximation
Accuracy of approximation
Quality of classification
0 (non-crisis) 293 293 293 1 1 1 (crisis) 128 128 128 1 1
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These results show that the data are very well dis- criminated among them (so the boundary region is empty for the two decision classes). Yet, the fact that a set of attributes discriminates well objects does not necessarily imply that a good classifier can be constructed on this set.
The core is consisted of four attributes: Inflation, Domestic Credit Growth, Real GDP per capita, and Bank Foreign Liabilities to Foreign Assets, which represent the most relevant attributes in the table. This result shows the importance of these four variables to forecast financial instability in a country. Moreover, they are well in line with previ- ous research. Demirgüç-Kant and Detragiache (1997) found that crisis tend to erupt when growth is low and inflation is high. Eichengreen and Arteta (2000) discover among the robust causes of emerg- ing banking crisis a rapid domestic credit growth and large bank liabilities relative to reserves. We have obtained 19 reducts from the table which con- tain 9–10 attributes. We have selected the reduct consisted of Central Bank Independence, Inflation, Domestic Credit Growth, Real GDP growth, Bank Foreign Liabilities to Foreign Assets, Real GDP per capita, World Growth, Real Interest Rate and Previous Crisis. The model has been selected attending to its better performance in terms of cor- rectly classified firms as well as in terms of eco- nomic interpretation. So we have obtained a reduced table to obtain the decision rules. The strategy we have followed to obtain the decision
Table 1 List of subintervals (quartiles)
Variable 1st 2nd
CRECIM. (�1, 2.9] (2.9, CBANKINDEP (�1, 0.37] (0.37 REAL INTEREST (�1, 0.33] (0.33 DOM.CREDIT.GROWTH (�1, 7.90] (7.90 BANK CASH REV. (�1, 0.02] (0.02 FOR_LIAB_REV (�1, 0.36] (0.36 GDP_GROWTH (�1, 2] (2, 4 INFLATION (�1, 2.81] (2.81 %NETKFLOWS (�1,�0.003] (�0. GDPPERHEAD (�1, 3144] (314
rules consists in the generation of a minimal subset of rules covering all the objects from the decision table. This strategy is implemented in the ROSE software. We have obtained 116 deterministic rules (63 for class 0 and the other ones for class 1). To interpret the rules, we have only selected the strongest rules (3.12%) for each decision class, thus we have only considered 40 rules. This way we have covered 85.5% objects in the table. Therefore, Table A.2 (see Appendix A) shows the strongest rules.
The decision model has been tested (using the 116 rules) on data from the testing test, i.e., on the 100 firms that have not been used to estimate the algo- rithm. The classification accuracy in percent of cor- rectly classified firms by this second set of rules is: 80%. This result is quite satisfactory comparing with previous analysis. Demirgüç-Kant and Detragiache (1997) obtained similar results and in general the corrected R-square is well below this percentage (Eichengreen and Arteta, 2000; Domaç and Martı́nez Peria, 2000, etc.).
Focusing in the role of the design of monetary policy in determining financial stability, we can observe that in 18 of the 19 reducts at least one of the three variables related with the design of the monetary policy (Exchange, Independence, and Monetarypol) appears. Given the co-linearity between them it is not strange that generally only one of them was chosen in each model. This result confirms the idea that the design of the monetary
3rd 4th
3.5] (3.5, 4.6] (4.6, +1) , 0.59] (0.59, 0.82] (0.82, +1) , 3.64] (3.64, 6.15] (6.15, +1) , 15.88] (15.88, 28.47] (28.47, +1) , 0.06] (0.06, 0.15] (0.15, +1) , 0.52] (0.52, 0.65] (0.65, +1)
] (4, 6] (6, +1) , 7.25] (7.25, 16.04] (16.04, +1) 003, 0.896] (0.896, 4724] (4724, +1) 4, 8180] (8180, 17,392] (17,392, +1)
Table 2 Number of rules that use the INDEPEN variable
Quartiles 1 2 3 4 Total
Non-crisis/crisis
D = 0 6 7 9 8 30 % 20.0 23.3 30.0 26.7 100.0 D = 1 5 7 7 3 22 % 22.7 31.8 31.8 13.6 100.0
Number of units classified by these rules
D = 0 74 29 34 55 192 % 38.5 15.1 17.7 28.6 100.0 D = 1 9 29 16 5 59 % 15.3 49.2 27.1 8.5 100.0
5 Non-linear probit/logit models can be developed by perform- ing a non-monotonic transformation of the variables or a transformation into nominal categorical variables.
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policy is a relevant variable in order to explain financial stability, as it was suggested in the paper of Garcı́a-Herrero and del Rio (2003).
Moreover, between the four variables that belong to the core there are two directly related with mon- etary policy: the level of inflation and the domestic credit growth.
Focusing in the chosen model we can see that the Central Bank Independence variable enters in 52 of the 116 rules. This represents the 45% of the total rules. However, in terms of objects covered by the rules (strength) represents the 59.6%. As we can see in Table 2, the percentage in terms of classified units in the rules for no crisis is 66% and in the crisis group 46%. So, results suggest that this variable play an important role in determining financial crisis.
But as shown in Table 2 not always a higher degree of independence is associated with financial stability. Seventy-four units with a degree of inde- pendency belonging to the lowest quartile showed financial stability, while 55 units in the highest quar- tile also showed stability. In these two extremes of the distribution we can see that only a reduced num- ber of crisis are associated, indicating that a clear independence or a clear dependency is associated almost always with financial stability. On the con- trary, the crisis are clearly associated with levels of independence in the second and third quartile of the distribution highlighting that no clear definition of the monetary policy objectives is a factor that contributes to the financial crisis. In other words, it is more important for financial stability that finan- cial agents know the reaction function on monetary policy rather than the function in itself. This result is independent on the level of inflation since there is a control variable accounting for this. A way to see
that central bank independence is not picking up the effect of the inflation variable is looking at the correlation between both variables. The coefficient of correlation, calculated with the original continu- ous variables is very low, 0.05. This coefficient could be influenced by outliers that play a different role when we use discrete variables. So we calculate a measure using the discretized variables and, although the result is not so strong (0.55% of cases show a distance lower than two in absolute terms) we can conclude that there are no clear correlation between central bank independence and inflation in our sample.
This result differs from the results obtained in previous researches by Garcı́a and del Rı́o who found a negative relationship between the degree of central bank independence and the emergence of financial crisis. A multivariate linear probit and logit models are used, respectively.5 Linear models do not have the flexibility to capture non-monotonic relationships as we have found, so it is reasonable that results differ as we have a much more flexible methodological approach.
5.3. Prediction of the insolvency of Spanish
non-life insurance companies
The information table for year 1 which consisted of 72 firms described with 17 ratios and assigned to a decision class (healthy – 1 or not – 0) was entered into an input file in ROSE. We have followed the same steps as in the first model. Therefore, the train- ing information table was entered into an input file in ROSE. In this model we have recoded the finan- cial ratios into qualitative terms (low, medium, high and very high) with corresponding numerical values such us 1, 2, 3 and 4 using the quartiles for the values of each variable. We want to make the same remarks described in Section 5.1 related to the selection of the discretization method (see Table 3).
The first results obtained from RS analysis of the coded information table were that the approxima- tion of the decision classes and their quality of clas- sification were equal to one:
Class Number of firms
Lower approximation
Upper approximation
Accuracy of approximation
Quality of classification
0 (failed firms) 36 36 36 1 1 1 (healthy firms) 36 36 36 1 1
Table 3 List of subintervals (quartiles) for financial ratios
Ratio 1� 2� 3� 4�
A1 (�1, 0.155] (0.155, 0.385] (0.385, 0.68] (0.68, +1) A5 (�1,�0.29] (�0.29,�0.005] (�0.005, 0.195] (0.195, +1) A6 (�1, 0.52] (0.52, 0.705] (0.705, 0.875] (0.875, +1) B3 (�1, 0.325] (0.325, 0.55] (0.55, 0.96] (0.96, +1) B6 (�1, 0.07] (0.07, 0.495] (0.495, 1.35] (1.35, +1) B7 (�1, 0.635] (0.635, 1.435] (1.435, 3.185] (3.185, +1) B8 (�1, 0.775] (0.775, 1.465] (1.465, 2.485] (2.485, +1) C1 (�1,�0.04] (�0.04, 0] (0, 0.04] (0.04, +1) C4 (�1, 0.005] (0.005, 0.13] (0.13, 0.41] (0.41, +1) C5 (�1, 0.005] (0.005, 0.095] (0.095, 0.33] (0.33, +1) C6 (�1,�0.245] (�0.245,�0.025] (�0.025, 0.05] (0.05, +1) C7 (�1,�0.03] (�0.03, 0.01] (0.01, 0.06] (0.06, +1) D1 (�1, 0.04] (0.04, 0.295] (0.295, 0.965] (0.965, +1) D4 (�1, 0.08] (0.08, 0.785] (0.785, 1.63] (1.63, +1) D6 (�1, 0.07] (0.07, 0.565] (0.565, 2.82] (2.82, +1) D7 (�1, 0] (0, 0.01] (0.01, 0.46] (0.46, +1) D8 (�1,0] (0, 0.355] (0.355, 0.435] (0.435, +1)
A. Sanchis et al. / European Journal of Operational Research 181 (2007) 1554–1573 1565
These results obtained show that the firms are very well discriminated among them (consequently, the boundary region is empty for the two decision classes). This fact can be explained because we have employed data 1 year prior to bankruptcy and therefore ratios for failed firms are substantially dif- ferent from the ratios of the healthy ones but, as we have previously mentioned for model 1, the fact that a set of attributes (ratios) discriminates well objects (firms) does not necessarily imply that a good clas- sifier can be constructed on this set. Another result is that none of the attributes are indispensable for the approximation of the two decision classes (so the core was empty). We have obtained 452 reducts from the table which contain 4–8 attributes. This result means that at least 9 attributes are redundant (and, therefore, they could be eliminated). Conse- quently, this fact shows the strong support of this approach in feature selection. The list of the fre- quencies of the attributes in the 452 reducts is the following one:
Attr. A1 A5 A6 B3 B6 B7 B8 C1 C
Freq 184 209 142 86 95 152 262 131 2
As we can see the ratios that have the highest fre- quency of occurrence (more than 40%) in reducts are B8, C5, D4, C4, A5, and C6. This fact indicates that these variables are highly discriminatory between solvent and insolvent firms in our sample confirming the importance, from a solvency view- point, of these questions: sufficient liquidity, correct rating, proper reinsurance and the need of having enough technical provisions.
These results are broadly in line with those obtained by Sanchis et al. (2003) that also high- lighted the role of liquidity, and correct rating and the need to have enough provisions when predicting insurance bankruptcy. However, reinsurance plays here a role that was not found by those authors.
We have selected the reduct consisted of A5, A6, B6, B8, C6, D8 taking into account two questions: the reduct should have a small number of attributes as possible and it should have the most significant attributes in our opinion for the evaluation of the companies (at least the selected reduct should
4 C5 C6 C7 D1 D4 D6 D7 D8
27 259 199 140 120 232 130 65 178
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contain one ratio of each group A, B, C or D and, if possible, the ratios with highest frequency of occur- rence within each group). So we have obtained a reduced table (see Table A.3 in Appendix A) (only six financial ratios) to obtain the decision rules. We have followed the same strategy to generate the decision rules as in the previous model. We have obtained 30 deterministic rules (see Table A.4 in Appendix A).
We want to mention that the large number of reducts obtained implies a very detailed analysis of the reducts to choose one of them in order to gener- ate the smallest number of stronger rules. Therefore, the first strategy we followed was to generate the minimal set of the decision rules considering the whole data set. We obtained 23 rules. Some of them were supported by only one object or by two objects and the classification accuracy of the 23-rules model was significantly worse. Consequently, we have decided to analyze the reducts and to obtain better classification results though the model employed contains more decision rules.
The 30-rules decision model has been tested on data from 2, 3, 4 and 5 years before the actual ratio values (year 1 or year prior to bankruptcy) that were used to obtain the decision rules (Dimitras et al., 1999). The classifications accuracies in percent of correctly classified firms by the set of 30 rules for the 5 years prior to the reference year (year 1) are shown in Table 4 at the end of Section 5.4.
5.4. Comparison of Rough Set approach with
discriminant analysis
We have compared rough set model with Dis- criminant Analysis (DA). Briefly, DA is a statistical technique used to classify objects into distinct groups on the basis of their observed characteristics. Basically, a linear discriminant function is devel- oped which will compute a ‘‘score’’ for an object. This function is a weighted linear combination of the object’s observed values on discriminating char- acteristics. These weights represent, essentially, the relative importance and impact of the various
Table 4 RS and DA results
Year 1 Year 2
Rough Set 100% 80.56% Linear discriminant function 81.86% 81.27% Quadratic discriminant function 67.48% 59.78%
characteristics. On the basis of its discriminant score, an object is then classified. Altman et al. (1981) provides a detailed description of DA and its financial applications.
RS and DA analysis require some assumptions but the ones required by RS approach are much weaker that the ones required by DA approach. This way, the discriminant analysis requires these restrictive assumptions: each group follows a multi- variate normal distribution, the covariance matrices of each group are identical, and, the mean vectors, covariance matrices, prior probabilities and misclas- sifications costs are known. These theoretical assumptions constitute ideal conditions in which DA should be applied and if they are violated, the methodology can be applied but the results obtained may be erroneous or inferior. Therefore, one advan- tage of RS theory is that it does not need restrictive assumptions and, consequently, it is more realistic which is manifested by better results of this approach.
Unfortunately in practice, violations of statistical assumptions of DA analysis occur regularly. How- ever, although these assumptions are not satisfied in the case of financial ratios, DA has provided good empirical results in real problems dealing with this kind of variables. This explains why this tech- nique is one of the most used in prediction problems and the reasons why it has been chosen.
To compare the two methods we have used two discriminant functions: a linear function and a qua- dratic function (Sanchis et al., 2003). Both functions have been derived using the original data table instead of the recoded one. The quadratic one has been developed due to covariance matrices are not equal, so results obtained by the linear model could be questioned. The classifications accuracies (prior probabilities and misclassifications costs are set for 0.5) in percent of correctly classified firms by the two discriminant functions and RS model for the 5 years prior to the reference year (year 1) are:
In general, results for the rough set model and linear discriminant model are quite similar and RS model has outperformed the quadratic model.
Year 3 Year 4 Year 5
76.36% 75.50% 65.85% 76.79% 75.34% 77.78% 73.02% 53.46% 75%
Table A.1 List of ratios
Ratio Definition
A1 (Capital + Reserves)/Total liabilities A5 Working capital/Total assets A6 Current assets/Total assets B3 Net premiums/Total assets B6 Provisions for benefit/Claims incurred B7 Net premiums/(Capital + Reserves) B8 (Capital + Reserves + Technical provisions)
/Earned premiums C1 Earnings before taxes/(Total liabilities �
Capital � Reserves) C4 Cash-flow/(Capital + Reserves) C5 Cash-flow/(Total liabilities � Capital � Reserves) C6 Accrued results/(Subscribed capital � Accrued results) C7 Earnings before taxes/(Capital + Reserves) D1 Provisions for benefit/Earned premiums D4 Technical provisions/Earned premiums D6 Technical provisions/(Capital + Reserves) D7 Technical provisions of cession/(Capital + Reserves) D8 Technical provisions for current risks/Earned premiums
A. Sanchis et al. / European Journal of Operational Research 181 (2007) 1554–1573 1567
6. Conclusions
We have presented a new approach to predict financial stability in a country and to predict insur- ance insolvency using rough sets. The results obtained for both models are quite satisfactory.
Through the exposition we have mentioned some advantages of this approach so we can conclude that this method is an effective tool for supporting managerial decision making in general. In the light of the experiments carried out, this method is a competitive alternative to existing prediction models for both problems that undoubtedly make it attrac- tive for application to the field of business classification.
Our empirical results in the insolvency prediction case show that rough set model offers better predic- tive accuracy than the quadratic discriminant model we have developed. The results obtained by the lin- ear discriminant model are comparable to the ones obtained by RS model. However, RS model does not require the pre-specification of a functional form, or the adoption of restrictive assumptions about the characteristics of statistical distributions of the variables and errors of the model. In short, by its nature, rough set approach makes working with imprecise variables possible. The flexibility of the decision rules with changes of the models over the time allows us to adapt them gradually to the appearance of new cases representing changes in the situation. Consequently, for some real-world problems, the method we have presented is more attractive than the discriminant analysis showing that it is a very robust technique especially in the areas of forecasting and classification decision problems.
In practical terms, the decision rules generated can be used to preselect companies or countries to examine more thoroughly, quickly and inexpen- sively, thereby, managing the financial user’s time efficiently. They can also be used to check and monitor insurance firms or countries as a ‘‘warning system’’ for insurance regulators, investors, man- agement, financial analysts, banks, auditors, policy holders and consumers.
Acknowledgements
We want to thank to the Institute of Computing Science of Poznan University of Technology for providing ROSE software and for helping us with the rough set analysis and to the anonymous
referees for the comments that have really improved this paper.
Appendix A. Data appendix
A.1. Financial crisis database
A.1.1. Dependent variable
Systemic and non-systemic banking crises dummy:
Equals one during episodes identified as in Caprio and Klingebiel (2003). They present information on 117 systemic banking crises (defined as much or all of bank capital being exhausted) that have occurred since the late 1970s in 93 countries and 51 smaller non-systemic banking crises in 45 coun- tries during that period. The information on crises is cross-checked with that of Domaç and Marti- nez-Peria (2000) and with IMF staff reports and financial news.
A.1.2. The Objective variables
* Monetary policy strategies: These variables (Exchange rate target, Monetary policy target) are dummies. The exchange rate target takes four values depending on the exchange rate regime: free float- ing, managed floating, pegged currencies and cur- rency board. The Monetary policy target equals one during periods in which targets were based on monetary aggregates, two when the objective was inflation, three when the two variables are into the objective function and zero in other cases, according
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to the chronology of the Bank of England survey of monetary frameworks, in Mahadeva and Sterne (2000). Since it provides a chronology for the 1990s, we have complemented it with information from other sources for the previous years. Regard- ing exchange rate arrangements, we use classifica- tions of exchange rate strategies in Reinhart and Rogoff (2002), Kuttner and Posen (2001), and Berg et al. (2002) for Latin America countries. Data for monetary and inflation targets were complemented with the information taken from Kuttner and Posen (2001) and Carare and Stone (2003). It should be
Table A.2 Decision rules for Model 1
# Rule Indep DCG Bank cash Liabil. Real GDP
Inflat. Inte
1 1 2 2 3 2 3 4 1 4 1 3 4 5 1 2 6 2 7 3 3 8 4 9 3 3 3 10 4 11 4 1 12 1 1 13 4 14 2 2 15 4 2 2 16 3 17 4 18 3 2 3 19 4 2 20 2 3 21 2 3 22 2 1 23 3 3 24 4 25 2 1 4 26 4 27 3 4 28 2 3 29 2 1 3 30 1 4 31 2 1 2 2 32 4 33 4 34 2 35 2 4 36 1 4 37 3 4 38 1 39 3 4 40 4 2 4
noted that some judgement has gone into the classi- fication of regimes.
* Central Bank Independence measures to what extent the central banks are legally independent according to their charters, following the approach of Cukierman et al. (1992). This variable goes from 0 (least independent) to 1 (most independent) and is taken from Cukierman et al. (1992), for the 1970s and 1980s.). For the 1990s, Mahadeva and Sterne (2000) and Cukierman et al. (2002). The index of independence is assumed to be constant through every year of each decade.
rest NKF GDP p/cap.
Prev. crisis World GDP
Class Streng.
3 0 21 0 30
0 0 20 0 0 9 0 0 15
2 0 0 25 1 0 10
3 0 0 10 0 9
4 1 3 0 10 0 0 9
1 0 0 13 2 1 0 10
0 0 16 0 11
3 4 0 15 3 1 0 11
0 10 0 0 9
1 0 0 9 1 1 5 3 2 1 5
1 1 1 6 3 3 1 10
2 1 4 1 4 1 4
1 3 1 6 2 1 5
1 4 3 1 7
1 4 1 2 1 1 4 1 1 1 1 4
4 3 1 6 0 3 1 4
1 1 4 4 3 1 5 1 2 1 4 2 1 5
1 4
Table A.3 Decision table for Model 2
Firms A5 A6 B6 B8 C6 D8 D
1 2 2 3 3 2 2 0 2 3 4 1 3 2 3 0 3 1 3 1 3 1 4 0 4 2 4 4 3 3 4 0 5 3 3 2 2 3 3 0 6 1 4 3 3 1 2 0 7 1 4 4 1 4 4 0 8 1 4 3 3 2 4 0 9 3 2 4 3 2 4 0 10 1 3 3 3 1 2 0 11 1 3 3 3 1 4 0 12 1 3 4 1 1 1 0 13 1 4 2 4 2 2 0 14 2 2 3 3 2 4 0 15 2 4 2 4 1 4 0 16 1 1 2 1 1 2 0 17 1 2 3 1 1 4 0 18 2 3 2 2 4 2 0 19 1 3 3 3 1 4 0 20 2 4 3 2 2 2 0 21 3 3 1 3 1 3 0 22 2 3 1 2 3 3 0 23 2 2 4 1 4 1 0 24 1 4 3 4 3 3 0 25 1 1 2 2 2 2 0 26 4 2 4 1 1 1 0 27 3 3 1 1 1 3 0 28 1 3 1 4 3 1 0 29 2 4 4 2 2 3 0 30 4 1 1 1 4 1 0 31 3 3 1 2 4 1 0 32 2 4 3 2 1 4 0 33 3 1 1 1 2 1 0 34 2 3 4 1 3 1 0 35 2 2 4 1 4 3 0 36 4 1 4 1 4 1 0 101 4 1 2 2 3 2 1 102 4 4 4 4 3 1 1 103 4 2 1 3 4 1 1 104 2 1 2 2 4 2 1 105 4 1 4 4 4 3 1 106 2 2 2 4 2 4 1 107 4 1 3 4 4 2 1 108 3 1 3 4 1 4 1 109 2 2 2 2 3 2 1 110 3 1 2 2 2 2 1 111 3 1 2 4 2 4 1 112 4 2 4 1 4 1 1 113 4 1 2 2 3 2 1 114 3 2 2 4 2 2 1 115 1 3 3 4 2 4 1 116 2 2 3 3 1 2 1 117 3 2 3 2 1 2 1 118 4 2 4 3 4 3 1 119 1 1 2 2 1 2 1 120 3 2 3 2 3 4 1 121 2 3 1 1 2 1 1
(continued on next page)
A. Sanchis et al. / European Journal of Operational Research 181 (2007) 1554–1573 1569
Table A.3 (continued)
Firms A5 A6 B6 B8 C6 D8 D
122 3 3 1 4 2 1 1 123 4 4 1 3 3 3 1 124 1 1 2 4 3 3 1 125 1 4 2 4 4 3 1 126 4 4 4 4 3 3 1 127 4 4 4 1 4 3 1 128 2 3 1 3 1 1 1 129 3 4 3 4 3 4 1 130 3 3 1 2 3 1 1 131 4 1 1 1 3 1 1 132 3 2 2 2 2 4 1 133 4 2 1 1 3 1 1 134 3 3 1 4 3 3 1 135 4 1 1 1 4 3 1 136 4 1 1 3 4 1 1
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A.1.3. Control variables
A.1.3.1. Macroeconomic variables. * Inflation: Per- centage change in the GDP deflator. Source: Inter- national Monetary Fund, International Financial Statistics, line 99bir.
Table A.4 Decision rules for Model 2
Rules A5 A6 B6 B8 C6 D8 D
1 1 3 1 0 2 2 4 0 3 1 4 3 0 4 1 3 0 5 3 2 0 6 1 2 2 0 7 1 1 4 1 0 8 3 4 0 9 1 1 0 10 2 4 0 11 2 3 0 12 4 2 0 13 4 1 0 14 1 1 0 15 3 1 0 16 4 3 1 17 3 4 1 18 2 2 1 19 4 3 1 20 4 3 1 21 1 4 2 1 22 1 2 3 1 23 2 2 1 24 2 1 1 1 25 3 1 2 1 26 2 2 1 1 27 4 2 4 1 28 2 3 1 1 29 2 3 1 1 30 3 4 2 1
* Real Interest Rate: Nominal interest rate minus inflation in the same period, calculated as the per- centage change in the GDP deflator. Source: Inter- national Monetary Fund, International Financial Statistics. Where available, money market rate (line
ecision Strength Firms
5 6, 10, 11, 17, 19 5 4, 23, 29, 34, 35 3 6, 8, 24 2 21, 27 5 1, 2, 8, 9, 14 1 25 2 30, 36 2 18, 31 4 7, 12, 16, 17 5 4, 15, 20, 29, 32 3 5, 22, 29 5 2, 8, 13, 20, 29 1 26 2 3, 28 2 27, 33 6 105, 118, 123, 126, 127, 135 6 108, 111, 114, 122, 129, 134 4 109, 117, 120, 132 4 103, 118, 123, 136 7 101, 102, 113, 123, 126, 131, 133 2 104, 107 2 124, 125 4 106, 109, 114, 132 2 121, 128 1 110 1 119 3 103, 112, 118 2 116, 128 1 130 1 115
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60B); otherwise, the commercial bank deposit inter- est rate (line 60l); otherwise, a rate charged by the Central Bank to domestic banks such as the dis- count rate (line 60).
* Net Capital Flows to GDP: Capital Account + Financial Account + Net Errors and Omissions. Source: International Monetary Fund, International Financial Statistics, lines (78bcd + 78bjd + 78cad).
* Real GDP per capita in 1995 US dollars: This variable is expressed in US dollars instead of PPP for reasons of data availability. GDP per capita in PPP was available only for two points in time. Source: The World Bank, World Tables; and EBRD, Transition Report, for some transition countries.
* Real GDP growth : Percentage change in GDP Volume (1995 = 100). Source: International Mone- tary Fund, International Financial Statistics (line 99bvp) where available; otherwise, The World Bank, World Tables; and EBRD, Transition Report, for some transition countries.
* World Real GDP growth: Percentage change in GDP Volume (1995 = 100). Source: International Monetary Fund, International Financial Statistics (line 99bvp) where available; otherwise, The World Bank, World Tables; and EBRD, Transition Report, for some transition countries.
A.1.3.2. Financial variables. * Domestic Credit growth: Percentage change in domestic credit, claims on private sector. Source: International Monetary Fund, International Financial Statistics, line 32d.
* Bank Cash to total assets: Reserves of Deposit Money Banks divided by total assets of Deposit Money Banks. Source: International Monetary Fund, International Financial Statistics, line 20 divided by lines (22a + 22b + 22c + 22d + 22f).
* Bank Foreign Liabilities to Foreign Assets: Deposit money banks foreign liabilities to foreign assets. Source: International Monetary Fund, Inter- national Financial Statistics, lines (26c + 26cl) divided by line 21.
* Previous Crisis: This variable equals zero if the country has not previous crisis; one, if the country has suffered one previous crisis; two, in case of two or three previous crisis, and, three, otherwise.
Insurance insolvency database shown in Table A.1.
Decision tables and decision rules tables shown in Tables A.2 and A.3.
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- Rough Sets and the role of the monetary policy in financial stability (macroeconomic problem) and the prediction of insolvency in insurance sector (microeconomic problem)
- Introduction
- The determinants of banking crises
- Financial ratios as explicatives variables of the insolvency in insurance sector
- The methodology: Main concepts of the Rough Set (RS) Theory
- Approximation of sets, accuracy and quality of approximation
- Reduction and dependency of attributes
- Decision rules
- Empirical results
- The data
- Prediction of financial instability
- Prediction of the insolvency of Spanishnon-life insurance companies
- Comparison of Rough Set approach with discriminant analysis
- Conclusions
- Acknowledgements
- Data appendix
- Financial crisis database
- Dependent variable
- The Objective variables
- Control variables
- Macroeconomic variables
- Financial variables
- References
The-Central-Bank-Policy-between-the-Price-Stability-Objective-and-Promoting-Financial-Stability_2014_Procedia-Economics-and-Finance.pdf
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1st International Conference 'Economic Scientific Research - Theoretical, Empirical and Practical Approaches', ESPERA 2013
The central bank policy between the price stability objective and promoting financial stability
Adina Cristea*, Iulia Lupua
aCentre for Financial and Monetary Research „Victor Slăvescu”, Calea 13 Septembrie 13, 050711,Bucharest, Romania
Abstract
The paper aims to emphasize the role of the monetary policy and the central bank's position concerning the financial stability in the new context created by the global financial crisis, and given that it pursues the price stability, as the primary objective. The analysis highlights the need to review the position of the central bank in order to promote a more proactive stance to deal with financial stability, beyond the traditional framework of regulation and supervision, but there is a risk of emerging conflicts derived from the pursuance of the primary objective (the price stability) while maintaining financial stability.
© 2014 The Authors. Published by Elsevier B.V. Selection and peer-review under responsibility of the Organizing Committee of ESPERA 2013.
Keywords: financial crisis; central banking; inflation targeting; governance; independence; non-standard monetary instruments, responsibility for financial stability
1. Introduction
Along with the outbreak of the global financial crisis in 2007, the “Great Moderation” period, characterized by a low macroeconomic volatility and a non-inflationary economic growth worldwide, has ended, and has begun a new
* Corresponding author. Tel.: 0-421.318.2419; fax: +0-421.318.2419. E-mail address: [email protected]
© 2014 The Authors. Published by Elsevier B.V. Open access under CC BY-NC-ND license. Selection and peer-review under responsibility of the Organizing Committee of ESPERA 2013
220 Adina Criste and Iulia Lupu / Procedia Economics and Finance 8 ( 2014 ) 219 – 225
stage of global transformation, for redefining the political and economic relations between countries, but also for restoring the priorities of the general policy to reduce the financial instability. On the one hand, the new macroeconomic framework underlines the importance of the clear and proper regulation, as the main condition for defense against the financial instability, and on the other hand, underlines the strengthened link between the financial stability and the macroeconomic policies, especially the monetary policy, to support it. Thus, it becomes obvious the increase of the Central Bank’s responsibility, with the monetary policy as an element of the macroeconomic policies’ mechanism.
The complex processes of expansion, liberalization and globalization of financial flows developed in the recent decades increasingly deepened the financial system, producing a widening gap between the financial economy and the real one, while the relationship between the financial and monetary stability (price stability) had complicated. Changes of the financial regimes (liberalization of financial flows) in most countries have made the financial factors, especially those related to the “boom-bust” cycle of credit or asset prices, to be generators of the economic fluctuations. Changes of the monetary regime during the “great moderation” were directed instead towards achieving monetary stability by keeping inflation and returns low, assuming that in this way would avoid the potential unsustainable development of the economy and would ensure stability of the financial system. In fact, the strong development of the financial sector weakened the ability of the inflation to report anomalies in economic activity development, while the furtherance of the monetary stability during the “great moderation” besides the fact that did not supported the financial stability but affected her, actually fostering speculative bubbles, given that, in a confident and optimistic background for businesses (especially for banks) was encouraged greater risk taking. In this context, it is necessary to reconsider the role of the central bank in terms of its primary objective of price stability, in conjunction with the promotion of the financial stability. This problem began to be raised especially after the crisis started in 2008. Although the central banks were those that protected the economies, they failed to support the recommencement of the economic recovery.
In this article we try to identify the new framework in which monetary policy can operate taking into account a reassessment of the role of the central bank given the increasing importance of the general objective of financial system stability, but also suspicions that central banks have allowed the appearance of conditions that led to the crisis. To better illustrate the research, the authors considered both a review of the literature on the relationship between financial and price stability, and a comparative analysis of how the major banks (European Central Bank - ECB the U.S. Federal Reserve - the Fed, and the Bank of England - BoE) relate to the issue of financial stability after the global financial crisis.
2. The changing role of central banks
The oldest central banks appeared at the end of the seventeenth century (Bank of Sweden in 1688, the Bank of England in 1694), followed by the Bank of France which appeared only in 1800 and other central banks that have been established by the end of the nineteenth century (Goodhart et al.1994). We mention, in order of their appearance, the central banks from Finland, the Netherlands, Portugal, Spain, Germany, Japan, and Italy. The number of central banks increased from 18 in 1900 to 161 in 1990 (Pringle et al.1993), most banks being relatively new, established since the mid-twentieth century. According to a study of the (Bank of International Settlements,2009) the last three central banks were established around the year 2000.
Predecessors of current central banks had completely different role than monetary policy, their main skill being to improve the government's ability to borrow money in times of war, many of them being established during some wars or immediately after their end (Clapham, 1944; Timberlake, 1993; Wilson 1957; Hamilton,1945). The central banks’ roles reflected the history, and were created to meet the needs of those times. Meanwhile, older functions such as monetary policy are different now, compared to beginning periods. Initially, the main functions of central banks’ early forms were the issuing of banknotes and governments’ bankers (these regnant banks became the classic choice for governments’ banking activity), and later some central banks (e.g. in Austria, France, Portugal and Spain) were established to rebuild the monetary stability and the currencies’ credibility, the primary motivation being survival, and not necessarily wider macroeconomic issues. In time these regnant banks became bankers of the banking system and for economic reasons they provided loans for bank customers to cover their lack of liquidity, turning into lenders of last resort, but also in banking system supervisors, different function from the current one
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only and for pursuing their own economic interest and not the protection of the system as a national goal. The emergence of public objectives is related to the late nineteenth and early twentieth century, when the establishment of central banks was made for public reasons. The introduction of the gold standard confirmed the role of central banks to ensure the convertibility of national goods and led to the abandonment of commercial purposes. The economic crisis brought about by two World Wars and a changed view on the role of government in economic management led to the establishment of many central banks (as public institutions) and the nationalization of many central banks. Monetary policy has acquired other meanings by introducing the gold standard, the supervisory and regulatory functions were obvious and straightforward, and the changing role of government in the economy has created the function of economic development.
The period after the crisis started in 2007 is not the first time when the role of central banks has been revised. Such an approach has taken place after the Second World War, but periodically thereafter, whereas the objectives and instruments of central banks received new life.
The weakening of the Bretton Woods system efficiency in the ̓60s highlighted the role of monetary policy to stabilize the economy, bringing it at least on the same rank with fiscal policy. The changes were most obvious in the '70s, years characterized by inflation and inflexible markets when central banks became independent, establishing monetary policy to ensure price stability. It was also introduced the exchange rate tool, and monetary policy aimed to give more flexibility for markets.
During 1980-2007, the central banks have enjoyed a growing credibility built on the positive results gained in this period: reducing inflation and maintaining it at low levels, alleviate recession episodes (the amplitude and the time). In this way, it was created the belief that monetary policy was the tool that was able to effectively reduce the economic fluctuations and set the necessary economic growth faster and more consistent, the central bank being considered the main or even the only institution that can fight with the inflationary phenomenon. Such beliefs have resulted in the formation of inflation targeting strategy that has spread around the world since 1990, and central bank independence was considered the condition to achieve such an objective.
After 2007, these qualities were affected, one of the major risks being the loss of central bank independence by many pressures on them to carry out activities that go beyond the institutional framework in which the y worked before. (Cecchetti,2013) notes that the central banks currently face serious risk of being forced to solve virtually any problem of macroeconomic and financial stability, although these institutions cannot solve structural problems. Such a risk concerns including political pressure exerted on the monetary authority to become, under the pretext of the financial stability policy, a component of the financing system of government.
3. The relationship between price stability and financial stability
Some authors believe that price stability should be a sufficient condition for financial stability (Schwartz, 1995) or that price stability promotes financial stability (Bordo and Wheelock,1995). As (Bordo, 2007) argues that price stability is a prerequisite for financial stability. According to the same approach, it is claimed that financial and price stability reinforces each other on the long run. Empirically it has been shown that many financial crises were caused by significant changes in the price level (Bordo et al.2000), and most banking crises occurred during the recession that often followed episodes of high inflation (Gorton,1988); Calomiris and Gorton,1991). This gave a motivation to central bankers to pursue price stability objective, which is considered adequate for the stability of the financial system.
On the other hand, in many papers (Borio and Lowe,20002; Borio et al.2003, Blinder,1988) it is pointed out that the view that price stability is beneficial for financial stability must be reversed. This idea is argued by the fact that the success of maintaining low inflation may induce a too optimistic view on the future development of the economy and the false perception about safety may excessively increase assets value. Based on this reasoning, we can conclude that stable inflation at low levels can make the financial system more vulnerable.
Another observation, which confirms the previous statement is that made by Japan's central bank governor, (Shirakawa, 2012): “obsessive focus on the stability of consumer prices in the short run as a mean to economic stability will actually have the reverse effect of increased instability”, the financial system becomes unstable, and by keeping expectations on long-term economic stability, increased indebtedness and imbalances between the maturities of assets and liabilities of financial institutions are stimulated.
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Experience demonstrates that the relation between financial and monetary stability is inconsistent: sometimes monetary stability promoted financial stability, sometimes, it embrittled it but concern over central bank's role in promoting financial stability is still an open issue.
4. General remarks on the central bank's role in promoting financial stability
Every economic policy has its specific objectives and instruments, but financial stability policy is rather vague, because there is no clear definition of financial stability and precise means of measurement. The objective of financial stability cannot be clearly formulated and formalized, as long as the targets are not well defined, such as price stability is formulated through inflation targeting strategy. Such a relationship is reflected in the sphere of accountability on monetary policy and financial stability policy. While the responsibility for monetary policy and its control belongs to a single institution, i.e. the prerogative of the central bank, the responsibility for financial stability and control for the tools for this area are usually distributed among several institutions.
Based on experience and different views on the role of central bank in promoting financial stability, one can summarize two general streams of thought on this topic. One is that the central bank should conduct proactively towards financial stability by extending the objectives of monetary policy so as to include financial stability (Eichengreen et al.2013) On the other hand, another school of thought argues that financial stability should be an objective by itself, followed either by an institution specially created for this purpose or by several institutions, cooperating, thus highlighting the difference between monetary policy and financial stability policy (Svensson,2013).
(Smaga,2013) emphasizes that, in principle, the degree of involvement of central banks in promoting financial stability refers to certain conditions: It has a legal basis on promoting financial stability, which is provided as a general objective in the statute of the
central bank; It has its own definition of financial stability; It uses a set of indicators of financial stability; It performs stress tests; It publishes reports on financial stability – to contribute to the stability of the financial system, to strengthen
cooperation between key institutions and enhance the transparency of the actions taken to promote financial stability;
It contributes to the operation of the payment system in the economy; It has a role in prudential supervision.
(Oosterloo and de Haan, 2003) have asserted that most of the central banks have no official definition for the financial stability or for the systemic risk, and the responsibility of these institutions regarding the financial stability is not explained in legal terms, but in general terms, as contributing, supporting the financial stability or as an obligation to ensure the proper functioning of the payment system. The study reveals that the publication of either a Financial Stability Report or sections into the Annual Reports on this subject can be considered as the main manner for the fulfilment of the central bank ̕ mandate in promoting financial stability.
According to (Borio,2011), prior to the global financial crisis, the central banks define the relationship between financial stability and monetary policy based on four statements: The price stability is a sufficient condition for macroeconomic stability - if the central bank manages to ensure
the price stability on the short-term (two years), in the absence of the exogenous shocks, then the economy can operate without any disturbances, considering that the price stability represents the best contribution of the monetary policy to the macroeconomic stability. This concept was specific to the “Great Moderation” period and it underpinned to the adoption of inflation targeting strategy.
There is a distinct separation between the financial stability and monetary stability functions. The central bank, as the lender of the last resort and liquidity provider, is considered the “treasurer” of the financial crises occurred, but there is a decoupling of these two functions regarding the crises prevention: monetary policy would ensure the price stability while the regulation and supervision policies would ensure the financial stability.
The interest rate, as the monetary policy instrument, is sufficient to influence the economic activity, the only operational instruments being the short-term interest rates and the expectations regarding its future evolution.
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If each central bank would respond by its policy to the needs and problems of their own country, then the global monetary stance would be appropriate. This idea of managing the internal problems is a version of the microprudential approach to the financial stability: if each independent institution (in this case, each country) is “healthy”, then the entire financial system (in this case, the world economy) will be safe and sound. The global financial crisis has changed the landscape in which central banks operate: before 2007 the inflation
targeting was considered the only and the best solution provided by a central bank for the macroeconomic stability objective, but after the global financial crisis, the central banks have been subject to a strong pressure concerning its involvement in adjusting the functioning of the financial markets.
5. The central banks ̕ experience in managing the global financial crisis
At the onset of the crisis, the central banks have responded by using the conventional measures, aggressively reducing the policy interest rates to prevent the risk of turning the disinflation into deflation phenomenon. Meanwhile, faced with a blockage in the interbank market, the major central banks (Fed, BoE, ECB) had to take direct charge of redistributing liquidity to meet the banks̕ needs. After Lehman Brothers shock propagation (in 2008), the crisis deepened, which required additional and special measures - unconventional monetary policy measures. The much-criticized decision taken by the ECB, that of raising the interest rates by 25 basis points, was then followed by a reduction of 50 basis points, in October, after the Lehman Brothers̕ bankruptcy. Fed has also asserted for a “close-to-zero interest rate” strategy, in summer 2010, before deciding, finally, a second wave of quantitative easing, in late of August 2010. In spring 2011, the ECB and the Fed restarted to announce the crisis-exit strategies. ECB began to normalize its monetary policy, increasing their representative interest rates by 25 basis points, in April and then in July, while in November and December to fall again by 25 basis points. The Fed position remained reticent, limited to the exposure of the different stages for exiting from the crisis. The deeper than expected economic recession led central banks to adopt accommodative monetary policy.
The diversity of the using the non-standard monetary policy measures are due to the differences regarding the financial systems (in the U.S. and UK, the financial system is dominated by the capital market, while in Europe, the financial system is dominated by the banking sector), the institutional framework and also regarding the perception of the risk ̕ evaluation undertaken by the central bank. In the Euro Area, the ECB attempted to correct those components of the monetary transmission mechanism that were most affected. On the other hand, the strategy applied in the U.S., was a blur of the boundary between the monetary policy and fiscal and financial policies. For Euro Area, such a framework would cause an increasing risk for altering the independence of the monetary authority.
Central banks underpin the economic activity both in the United States and in Europe. Given the almost non- existent leeway to cut interest rates, their main resource is to multiply the non-standard monetary policy instruments, the first consequence of that behaviour being an increasing of the size of the central bank̕ s balance sheet. However, the content of the measures differ from one central bank to another. Bank of England and Fed primarily aim to reduce the long-term interest rates in order to improve the financing conditions and to stimulate the private investment.
In the Euro Area, the objective is also to reduce the credit cost, but the action is focused on the banking sector, the main source of funding for the non-financial corporation in the Eurozone. However, by the announcement of the government securities acquisition program in the secondary market (Outright Monetary Transactions), on September 6, 2012, the monetary policy in the Euro Area experienced a turning point in the sense that the ECB has no limits on its interventions in bond markets. This decision is taken to ensure the monetary policy transmission mechanism in the Euro Area countries. Despite these measures, the economic recovery in the United States is weak and the economic activity in the euro area and UK is slow again. On the one hand, the developed economies, including the United States, are probably not completely out of the liquidity trap, which limits the effectiveness of the monetary policy. On the other hand, the stimulation made by the monetary policy is not enough to compensate an increasingly restrictiveness of the fiscal policy, especially in the Euro Area and UK.
ECB has chosen to support banks, providing liquidity in the banking system and not applying the quantitative easing, like the Fed or BoE, which is a measure directed toward providing monetary incentives when the interest
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rate is close to zero. The motivation for such a decision is that the banking sector is dominant in the Eurozone and so it should ensure continuously the financing to the private sector. The ECB did not intend to intervene directly in the assets market, but to ensure both a proper functioning of the monetary transmission mechanism in the Euro Area and correcting the malfunctions of various segments of the financial market.
The implementing of the conventional and unconventional measures of monetary policy, at the beginning of the global financial crisis and later, has suppressed both the financial deterioration and the economic activity restraining. However, the central bank's role was that of providing time to adopt adjusting measures for more general crisis consequences. They are not the solution to the crisis consequences, but for providing time.
In the context of the global crisis, one of the consequences derived from the measures applied by the central banks, is the expanding of their responsibility to the political area. The decision to implement quantitative easing measures by purchasing of some sort of securities looks like a subsidy of those who are in debt, requiring more political and democratic control. Also, the responsibility of the central banks shifts from the carrying out the monetary policy to the financial stability restoring. Such an extended operating area means an increasing of the central banks̕ constraints, by affecting their independence.
The consequences induced by the global financial crisis have shown not only that the restoring of the financial stability involves high costs borne primarily by central banks, but also that the standard model regarding the central bank's role, applied during the “Great Moderation”, should be reconsidered based on the interlinkages between monetary policy, fiscal policy and regulatory policy. (Ceccheti,2013) drew attention to these relationships:
the monetary policy influences the fiscal policy through the central bank’s balance sheet; the fiscal policy influences the monetary and regulatory policies through the government options regarding
its financing sources; the monetary policy, through its influence on balance sheets, influences the regulatory policy; the regulatory policy, through its dealing with the sovereign debt, influences the fiscal policy; the regulatory policy influences the monetary policy by modifying the borrowing costs.
Besides these observations, in the post-crisis environment, it is noticed the need for implementing the macro- prudential policies aimed at the financial stability objective, as limiting the systemic risk, and which are designed for the financial system, thus including also the interactions between the real economy and the financial economy.
The economic policies̓ instruments aimed at promoting the financial stability (those specific to the fiscal policy, monetary policy, regulatory policy, etc.) can be brought together under the umbrella of macroprudential policy. One of the most important tools that convey information on macroprudential policy is considered the Financial Stability Report, a document published by most central banks. Its publication is the specific responsibility of a central bank, and that is an argument for that institution to play a key role in the macroprudential supervision.
On the other hand, the central bank involvement in promoting the financial stability must be established between certain limits imposed by the mandate of the price stability. Such a conflict is especially noticeable when it plays the role of lender of last resort. Therefore, a challenge for the next period is that to disentangle the central bank's mandate regarding the financial stability.
Conclusions
More and more central banks began to expand their responsibilities, assuming the role of stabilizing the financial system, turning somehow to the reason for which the first central banks have been established, namely for government financing during crisis (specifically, for war-funding).
The conflict between the price stability and the financial stability is also reflected by the different time horizon for which they are designed. Monetary policy is usually set for a period of 2-3 years, which is consistent with the economic cycle, while the risks and imbalances in the financial system accumulate during a longer period, causing the so-called financial cycle, which can contain several economic cycles. A solution to this discrepancy could be widening the timescale for the price stability objective.
Many central banks pursue, in addition to the price stability objective, the economic development, and therefore they take certain measures concerning the use of resources, which could lead to the failure of stabilizing the short- term inflation and maintaining a sustainable resource use in the long-term. Taking into account the financial stability as a supplementary objective and if the economic and financial cycles go in different directions, then it could be
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generated conflicts between the stabilizing prices and the resource management, as short-term objectives, and financial stability, as long-term objective.
One of the major challenges for central banking refers not only to the potential conflict between the price stability and the financial stability, but also to the broadening of the operational framework by actions performed by central banks toward the restoring of the financial system. If, theoretically, there is the concern that by expanding the central bank’s balance sheet, it will be affected its primary objective, the experience of the recent years shows that the real risk of such actions is the impairment of the central bank's independence, because an excessive expansion of the central bank’s responsibilities means a greater involvement in the political arena.
For central banking, the financial stability remains of fundamental interest. The central banks should ensure a balance between maintaining the price stability, as its primary objective, and promoting the financial stability, which is a more general objective. The latter is found within the area of concerns of those institutions regarded as “safety net”. With globalization, it has become a prerequisite for promoting the financial stability that the central banks must collaborate with other institutions and financial authorities to exchange information on common interest for an effective action to prevent and to manage potential crises.
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Time-varying monetary-policy rules and financial stress Does financial.pdf
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Contents lists available at SciVerse ScienceDirect
Journal of Financial Stability
j o u r n a l h o m e p a g e : w w w . e l s e v i e r . c o m / l o c a t e / j f s t a b i l
ime-varying monetary-policy rules and financial stress: Does financial nstability matter for monetary policy?
aromír Baxa a,b, Roman Horváth a,∗, Bořek Vašíček c
Institute of Economic Studies, Charles University, Prague, Czech Republic Institute of Information Theory and Automation, Academy of Sciences of the Czech Republic, Czech Republic Czech National Bank, Czech Republic
r t i c l e i n f o
rticle history: eceived 3 January 2011 eceived in revised form 4 September 2011 ccepted 5 October 2011 vailable online 12 October 2011
EL classification: 43 52 58
a b s t r a c t
We examine whether and how selected central banks responded to episodes of financial stress over the last three decades. We employ a recently developed monetary-policy rule estimation methodology which allows for time-varying response coefficients and corrects for endogeneity. This flexible frame- work applied to the USA, the UK, Australia, Canada, and Sweden, together with a new financial stress dataset developed by the International Monetary Fund, not only allows testing of whether central banks responded to financial stress, but also detects the periods and types of stress that were the most worrying for monetary authorities and quantifies the intensity of the policy response. Our findings suggest that central banks often change policy rates, mainly decreasing them in the face of high financial stress. How- ever, the size of the policy response varies substantially over time as well as across countries, with the 2008–2009 financial crisis being the period of the most severe and generalized response. With regard to
eywords: inancial stress aylor rule onetary policy
the specific components of financial stress, most central banks seemed to respond to stock-market stress and bank stress, while exchange-rate stress is found to drive the reaction of central banks only in more open economies.
© 2011 Elsevier B.V. All rights reserved.
p s a m s l a d f
i i o a b
ime-varying parameter model ndogenous regressors
. Introduction
The recent financial crisis has intensified the interest in xploring the interactions between monetary policy and financial tability. Official interest rates were driven sharply to historical ows, and many unconventional measures were used to pump iquidity into the international financial system. Central banks pur- ued monetary policy under high economic uncertainty coupled ith large financial shocks in many countries. The financial crisis
lso raised new challenges for central bank policies, in particu- ar the operationalization of issues related to financial stability or monetary-policy decision making (Goodhart, 2006; Borio and rehmann, 2009).
This paper seeks to analyze whether and how monetary policy nterest rates evolved in response to financial instability over the
ast three decades. The monetary policies of central banks are likely o react to financial instability in a non-linear way (Goodhart et al., 009). When a financial system is stable, the interest-rate-setting
∗ Corresponding author. E-mail address: [email protected] (R. Horváth).
d n s
m
572-3089/$ – see front matter © 2011 Elsevier B.V. All rights reserved. oi:10.1016/j.jfs.2011.10.002
rocess largely reflects macroeconomic conditions, and financial tability considerations enter monetary policy discussions only to
limited degree. On the other hand, central banks may alter their onetary policies to reduce financial imbalances if these become
evere. In this respect, Mishkin (2009) questions the traditional inear-quadratic framework1 when financial markets are disrupted nd puts forward an argument for replacing it with non-linear ynamics describing the economy and a non-quadratic objective unction resulting in non-linear optimal policy.
To address the complexity of the nexus between monetary pol- cy and financial stability as well as to evaluate monetary policy n a systematic manner, this paper employs the recently devel- ped time-varying parameter estimation of monetary-policy rules, ppropriately accounting for endogeneity in policy rules. This flexi- le framework, together with a new comprehensive financial stress
ataset developed by the International Monetary Fund, will allow ot only testing of whether central banks responded to financial tress, but also quantification of the magnitude of this response
1 That is, linear behavior of the economy and a quadratic objective function of the onetary authority.
1 ncial
a w
c e t ( t f H a h t r s
e S w r
2
e ( m
2 t
l m s s
b t o c t i t ( e fi m e t c a a S 2
b
t i B a
a i s p p l r fi n i a o s A i p a s a m i r w r t c a a a c c b e r d t r c l w t w i ( e w a a s s n
i p
18 J. Baxa et al. / Journal of Fina
nd detection of the periods and types of stress that were the most orrying for monetary authorities.
Although theoretical studies disagree about the role of finan- ial instability for central banks’ interest-rate-setting policies, our mpirical estimates of the time-varying monetary-policy rules of he US Fed, the Bank of England (BoE), the Reserve Bank of Australia RBA), the Bank of Canada (BoC), and Sveriges Riksbank (SR) show hat central banks often alter the course of monetary policy in the ace of high financial stress, mainly by decreasing policy rates.2
owever, the size of this response varies substantially over time s well as across countries. There is some cross-country and time eterogeneity as well when we examine central banks’ considera- ions of specific types of financial stress: most of them seemed to espond to stock-market stress and bank stress, and exchange-rate tress drives central bank reactions only in more open economies.
The paper is organized as follows. Section 2 discusses related lit- rature. Section 3 describes our data and empirical methodology. ection 4 presents our results. Section 5 concludes. An appendix ith a detailed description of the methodology and additional
esults follows.
. Related literature
First, this section gives a brief overview of the theory as well as mpirical evidence on the relationship between monetary policy rules) and financial instability. Second, it provides a short sum-
ary of various measures of financial stress.
.1. Monetary policy (rules) and financial instability – some heories
Financial friction, such as unequal access to credit or debt col- ateralization, is recognized as having important consequences for
onetary policy transmission, and Fisher (1933) has already pre- ented the idea that adverse credit-market conditions can cause ignificant macroeconomic disequilibria.
During the last two decades, the effects of monetary policy have een studied mainly within New Keynesian (NK) dynamic stochas- ic general equilibrium (DSGE) models, which assume the existence f nominal rigidities. The common approach to incorporating finan- ial market friction within the DSGE framework is to introduce he financial accelerator mechanism (Bernanke et al., 1996, 1999), mplying that endogenous developments in credit markets work o amplify and propagate shocks to the macro economy. Tovar 2009) emphasizes that the major weakness of the financial accel- rator mechanism is that it only addresses one of many possible nancial frictions. Goodhart et al. (2009) note that many NK DSGE odels lack the financial sector completely or model it in a rather
mbryonic way. Consequently, more recent contributions within his stream of literature have examined other aspects of finan- ial friction, such as balance sheets in the banking sector (Choi nd Cook, 2004), the portfolio-choice issue with complete (Engel nd Matsumoto, 2009) or incomplete markets (Devereux and
utherland, 2007), and collateral constraints (Iacovello and Neri, 010).3
A few studies focus more specifically on the relationship etween the monetary-policy stance (or the monetary-policy rule)
2 Our choice of countries is based on data availability and on the suitability of he data for our econometric framework. Due to limited data availability, we do not nclude the Reserve Bank of New Zealand, the ECB, and emerging countries. The ank of Japan could not be included either, given that its policy rates were flat for n extended period. 3 A survey of this literature is provided by Tovar (2009).
t fi t o c t d b a a s
Stability 9 (2013) 117– 138
nd financial stability. However, they do not arrive at a unan- mous view of whether a monetary-policy rule should include ome measure of financial stability. Brousseau and Detken (2001) resent an NK model where a conflict arises between short-term rice stability and financial stability due to a self-fulfilling belief
inking the stability of inflation to the smoothness of the interest- ate path and suggests that monetary policy should react to nancial instability. Akram et al. (2007) investigate the macroeco- omic implications of pursuing financial stability within a flexible
nflation-targeting framework. Their model, using a policy rule ugmented by financial-stability indicators, shows that the gains f such an augmented rule vis-à-vis the rule without financial- tability indicators highly depends on the nature of the shocks. kram and Eitrheim (2008) build on the previous framework, find-
ng some evidence that the policy response to housing prices, equity rices or credit growth can cause high interest-rate volatility and ctually lower financial stability in terms of indicators that are ensitive to interest rates. Cecchetti and Li (2008) show, in both
static and dynamic setting, that a potential conflict between onetary policy and financial supervision can be avoided if the
nterest-rate rule takes into account (procyclical) capital-adequacy equirements, in particular, that policy interest rates are lowered hen financial stress is high. Bauducco et al. (2008) extend the cur-
ent benchmark NK model to include financial systems and firms hat require external financing. Their simulations show that if a entral bank responds to financial instability by policy easing, it chieves better inflation and output stabilization in the short term t the cost of greater inflation and output volatility in the long term, nd vice versa. For the US Fed, Taylor (2008) proposes a modifi- ation of the standard Taylor rule to incorporate adjustments to redit spreads. Teranishi (2009) derives a Taylor rule augmented y the response to credit spreads as an optimal policy under het- rogeneous loan-interest-rate contracts. He finds that the policy esponse to a credit spread can be both positive and negative, epending on the financial structure. However, he also proposes hat when nominal policy rates are close to zero, a commitment ather than a discretional policy response is the key to reducing redit spreads. Christiano et al. (2008) suggest augmenting the Tay- or rule with aggregate private credit and find that such a policy
ould raise welfare by reducing the magnitude of the output fluc- uations. Cúrdia and Woodford (2010) develop a NK DSGE model ith credit friction to evaluate the performance of alternative pol-
cy rules that are augmented by a response (1) to credit spreads and 2) to aggregate the volume of private credit in the face of differ- nt shocks. They argue that the response to credit spreads can be elfare improving, but the optimal size of such a response is prob-
bly rather small. Like Teranishi (2009), they find little support for ugmenting the Taylor rule by the credit volume, given that the ize and even the sign of the desired response is sensitive to the ources of shock and their persistence, which is information that is ot always available during operational policy making.
A related stream of literature focuses on the somewhat narrower ssue of whether or not monetary policy should respond to asset rices. Bernanke and Gertler (1999, 2001) argue that the stabiliza- ion of inflation and output provides a substantial contribution to nancial stability and that there are few, if any, gains to responding o asset prices. Faia and Monacelli (2007) extend the model devel- ped by Bernanke and Gertler (2001) by a robust welfare metric, onfirming that strict inflation stabilization offers the best solu- ion. Cecchetti et al. (2000) take the opposite stance, arguing that evelopments in asset markets can have a significant impact on
oth inflation and real economic activity, and central banks might chieve better outcomes by considering asset prices provided they re able to detect asset-price misalignments. Borio and Lowe (2002) upport this view, claiming that financial imbalances can build up
ncial
e t d p b a t R f
2 e
c w B s a C 2 t f t i r i a r r s s r p t F e m
o a s c o
u ( B F G fi t i w i C m r t H a
r
b J r b d f i t s m p i a m t s
2
b d b e a R ( s
d s f c c t r c a
i i a b i t b a h e i E A
T m a r f
J. Baxa et al. / Journal of Fina
ven in a low-inflation environment, which is normally favorable o financial stability. The side effect of low inflation is that excess emand pressures may first appear in credit aggregates and asset rices rather than consumer prices, which are normally considered y policy makers. Gruen et al. (2005) argue that responding to an sset bubble is feasible only when the monetary authority is able o make a correct judgment about the process driving the bubble. oubini (2006) and Posen (2006) provide a summary of this debate
rom a policy perspective.
.2. Monetary policy (rules) and financial instability – empirical vidence
The empirical evidence on central banks’ reactions to finan- ial instability is rather scant. Following the ongoing debate about hether central banks should respond to asset-price volatility (e.g. ernanke and Gertler, 1999, 2001; Cecchetti et al., 2000), some tudies have tested the response of monetary policy to different sset prices, most commonly stock prices (Rigobon and Sack, 2003; hadha et al., 2004; Siklos and Bohl, 2008; Fuhrer and Tootell, 008). They find some evidence either that asset prices entered he policy-information set (because they contain information about uture inflation) or that some central banks were directly trying o offset these disequilibria.4 All of these papers estimate time- nvariant policy rules, which means that they test a permanent esponse to these variables. However, it seems more plausible that f central banks respond to asset prices, they do so only when sset-price misalignments are substantial; in other words, their esponses are asymmetric. There are two additional controversies elated to the effects of asset prices on monetary-policy deci- ions. The first concerns the measure, in particular whether the tock-market index that is typically employed is sufficiently rep- esentative, or whether some other assets, in particular housing rices, should be considered as well. The second issue is related o the (even ex-post) identification of asset-price misalignment. inally, it is likely that the perception of misalignments is influ- nced by general economic conditions and that a possible response ight evolve over time. Detken and Smets (2004) summarize some stylized facts
n macroeconomic and monetary-policy developments during sset-price booms. Overall, they find that monetary policy was ignificantly looser during high-cost booms that were marked by rashes of investment and real-estate prices in the post-boom peri- ds.
A few empirical studies measure the monetary-policy response sing broader measures of financial imbalances. Borio and Lowe 2004) estimate the response of four central banks (the Reserve ank of Australia, the Bundesbank, the Bank of Japan, and the US ed) to imbalances proxied by the ratio of private-sector credit to DP, inflation-adjusted equity prices, and their composite. They nd either negative or ambiguous evidence for all countries except he USA, confirming that the Fed responded to financial imbalances n an asymmetric and reactive way, i.e., that the federal funds rate
as disproportionately lowered in the face of imbalance unwind- ng, but was not tightened beyond normal as imbalances built up. ecchetti and Li (2008) estimate a Taylor rule augmented by a easure of banking stress, in particular the deviation of leverage
atios (total loans to the sum of equity and subordinated debt;
otal assets to the sum of bank capital and reserves) from their odrick–Prescott trend. They find some evidence that the Fed djusted the interest rate to counteract the procyclical impact of a
4 A similar but somewhat less polemic debate applies to the role of exchange ates, especially for small, open economies (Taylor, 2001).
t o i m F p t
Stability 9 (2013) 117– 138 119
ank’s capital requirements, while the Bundesbank and the Bank of apan did not. Bulíř and Čihák (2008) estimate the monetary-policy esponse to seven alternative measures of financial-sector vulnera- ility (crisis probability, time to crisis, distance to default or credit efault swap spreads) in a panel of 28 countries. Their empirical ramework is different in the sense that the monetary-policy stance s proxied along the short-term interest rate by measures of domes- ic liquidity, and external shocks are controlled for. In the panel etting, they find a statistically significant negative response to any variables representing vulnerability (policy easing) but, sur-
risingly, not in country-level regressions. Belke and Klose (2010) nvestigate the factors behind the interest-rate decisions of the ECB nd the Fed during the current crisis. They conclude that the esti- ated policy rule was significantly altered only for the Fed, and
hey put forward that the ECB gave greater weight to inflation tabilization at the cost of some output loss.
.3. Measures of financial stress
The incidence and determinants of different types of crises have een typically traced in the literature by a means of narrative evi- ence (expert judgment). This has sometimes been complemented y selected indicators (exchange rate devaluation or the state of for- ign reserves) that point to historical regularities (e.g., Eichengreen nd Bordo, 2002; Kaminsky and Reinhart, 1999; Reinhart and ogoff, 2008; Laeven and Valencia, 2008). The empirical studies e.g., Goldstein et al., 2000) used binary variables that were con- tructed based on these narratives.
Consequently, some contributions strived to provide more ata-driven measures of financial stress. Most of the existing tress indices are based on high-frequency data, but they dif- er in the selected variables (bank capitalization, credit ratings, redit growth, interest rate spreads or volatility of different asset lasses), country coverage, and the aggregation method. An impor- ant advantage of continuous stress indicators is that they may eveal periods of small-scale stress that did not result in full-blown rises and were neglected in studies based on binary crisis vari- bles.
The Bank Credit Analyst (BCA) reports a monthly financial stress ndex (FSI) for the USA that is based on the performance of bank- ng shares compared to the whole stock market, credit spreads nd the slope of the yield curve, and new issues of stocks and onds and consumer confidence. JP Morgan calculates a Liquid-
ty, Credit and Volatility Index (LCVI) based on seven variables: he US Treasury curve error (the standard deviation of the spread etween on-the-run and off-the-run US Treasury bills and bonds long the entire maturity curve), the 10-year US swap spread, US igh-yield spreads, JP Morgan’s Emerging Markets Bond Index, for- ign exchange volatility (the weighted average of the 12-month mplied volatilities of several currencies), the Chicago Board of xchange VIX equity volatility index, and the JP Morgan Global Risk ppetite Index.
Illing and Liu (2006) develop a comprehensive FSI for Canada. heir underlying data cover equity, bond, and foreign exchange arkets as well as the banking sector. They use a standard measure
nd refined measure of each stress component, where the former efers to the variables and their transformations that are commonly ound in the literature, while the latter incorporates adjustments hat allow for better extraction of information about stressful peri- ds. They explore different weighting schemes to aggregate the ndividual series (factor analysis, the size of the corresponding
arket for total credit in the economy, variance-equal weighting). inally, they perform an expert survey to identify periods that were erceived as especially stressful, confirming that the FSI matches hese episodes very well.
1 ncial
a t t d a fi m i C a e i o p o a
l ( d t a v t c r t v m o e e d a h m
3
3
i i u v t 1
r e T m p u m D m i a
(
w b ( g o i p f a c b r 2 t s
a s u i t b d t d O a
b f c m f ( c
spread (the difference between short-term and long-term government bonds), TED spread (the difference between inter- bank rates and the yield on Treasury bills), banking beta
6 Borio and Disyatat (2009) characterize unconventional policies as policies that affect the central bank’s balance sheet size and composition and that can be insu- lated from interest rate policy (the so-called “decoupling principle”). One common example of such a policy (not necessarily used during times of crisis) is sterilized exchange-rate intervention. Given that we are looking not at a single episode of stress, but rather want to identify whether monetary authorities deviated from sys- tematic patterns (the policy rule) during these periods (by responding to indicators of financial stress), we need to use a consistent measure of policy action that is adjusted during periods of financial stress, though other measures may be in place as well. Therefore, we assume that the monetary-policy stance is fully reflected in the interest rate, and we are aware that it might be subject to downward bias on the financial-stress coefficient. The reader may want to interpret our results on the importance of financial stress for interest-rate setting as a conservative estimate.
7 There are other policy measures that can be used as a reactive or pre-emptive response to financial stress, such as regulatory or administrative measures, although their effects are likely to appear only in the longer term and cannot be reasonably included in our empirical analysis.
8
20 J. Baxa et al. / Journal of Fina
For the Fed Board of Governors, Carlson et al. (2009) propose framework similar to the option-pricing model (Merton, 1974) hat aims to provide the distance-to-default of the financial sys- em, the so-called Index of Financial Health. The method uses the ifference between the market value of a firm’s assets and liabilities nd the volatility of the asset’s value to measure the proximity of a rm’s assets to being exceeded by their liabilities. They apply this easure to 25 of the largest US financial institutions, confirming
ts impact on capital investments in the US economy. The Kansas ity Fed developed the Kansas City Financial Stress Index (Hakkio nd Keeton, 2009), which is published monthly and is based on leven variables (seven spreads between different bond classes by ssuers, risk profiles and maturities, correlations between returns n stocks and Treasury bonds, expected volatility of overall stock rices, volatility of bank stock prices, and a cross-section dispersion f bank stock returns) that are aggregated by principal component nalysis.
Finally, the International Monetary Fund (IMF) recently pub- ished financial stress indices for various countries. Cardarelli et al. 2011) propose a comprehensive index based on high-frequency ata where the price changes are measured with respect to heir previous levels or trend values. The underlying variables re standardized and aggregated into a single index (FSI) using ariance-equal weighting for each country and period. The FSI has hree subcomponents: the banking sector (the slope of the yield urve, TED spread, and the beta of banking-sector stocks), secu- ities markets (corporate bond spreads, stock-market returns and ime-varying volatility of stock returns) and exchange rates (time- arying volatility of NEER changes). Balakrishnan et al. (2009) odify the previous index to account for the specific conditions
f emerging economies, on the one hand including a measure of xchange rate pressures (currency depreciation and decline in for- ign reserves) and sovereign debt spread, and on the other hand ownplaying the banking-sector measures (slope of the yield curve nd TED spread).5 We will use the former index, given its compre- ensiveness as well as its availability for different countries (see ore details below).
. Data and empirical methodology
.1. The dataset
Given the frequency of monetary policy committee meetings n most central banks, we use monthly data (due to unavailabil- ty of all monthly series for a sufficiently long time period, we se quarterly data for Sweden and Canada). The sample periods ary slightly due to data availability (the US 1981:1M–2009:6M; he UK 1981:1M–2009:3M; Australia 1983:3M–2009:5M; Canada 981:1Q–2008:4Q; Sweden 1984:2Q–2009:1Q).
The dependent variable is typically an interest rate closely elated to the official (censored) policy rate, in particular the fed- ral funds rate (3M) for the USA, the discount rate (three-month reasury bills) for the UK, Canada, and Sweden, and the three- onth RBA-accepted bills rate for Australia. It is evident that the
olicy rate is not necessarily the only instrument that central banks se, especially during the 2008–2009 global financial crisis, when any unconventional measures were implemented (see Borio and isyatat, 2009; Reis, 2010). To address this issue in terms of esti-
ated policy rules, for a robustness check we use the interbank
nterest rate (at a maturity of three months). While both rates re used in empirical papers on monetary-policy rule estimation
5 The IMF Financial Stress Index has recently been applied by Melvin and Taylor 2009) to analyze exchange rate crises.
o m
g v t a v
Stability 9 (2013) 117– 138
ithout great controversy, the selection of the interest rate ecomes a more delicate issue during periods of financial stress Taylor, 2008). While the former is more directly affected by enuine monetary-policy decisions (carried out by open market perations), the latter additionally includes liquidity conditions on nterbank markets and, as such, can be affected by unconventional olicies, though these are usually insulated (often intentionally) rom policy interest rates.6 This is a drawback but also a potential dvantage of this alternative dependent variable. On the one hand, hanges in official policy rates may not pass through fully to inter- ank interest rates, in particular when the perceived counterparty isk is too high and credit spreads widen (see Taylor and Williams, 009). On the other hand, the interbank rate may also incorporate he impact of policy actions, such as quantitative easing aimed at upplying additional liquidity into the system.7
Inflation is measured as the year-on-year change in the CPI, part from for the United States, where we use the personal con- umption expenditures (PCE) price index, and Sweden, where nderlying CPIX inflation (which excludes households’ mortgage-
nterest expenditures and the direct effects of changes in indirect axes and subsidies from the CPI) is used.8 The output gap is proxied y the gap of the seasonally adjusted industrial production index erived by the Hodrick–Prescott filter with a smoothing parame- er set to 14,400.9 For Sweden and Canada, where we use quarterly ata, the output gap was taken as reported in the OECD Economic utlook (production function method based on NAWRU – non- ccelerating wage rate of unemployment).
We proxy financial stress by means of the FSI provided recently y the IMF (Cardarelli et al., 2011), which is a consistent measure or a wide range of countries but, at the same time, is sufficiently omprehensive to track stress of a different nature. It includes the ain components of financial stress in an economy and is available
or a reasonably long period to be used for our empirical analysis see Fig. 1). We use both the overall index, which is a sum of seven omponents, as well as each sub-index and component separately:
(i) Banking-related sub-index components: the inverted term
For Australia, the monthly CPI is not available because both the Reserve Bank f Australia and the Australian Bureau of Statistics only publish quarterly data. The onthly series was obtained using linear interpolation of the CPI index. 9 The industrial production cycle had to be used as a proxy for the output gap
iven that GDP data are not available at monthly frequency. Though a bit more olatile, it is highly correlated with the output gap from GDP (comparison at quar- erly frequency). Moreover, industrial production data tend to be revised less often nd to a lesser extent than the GDP data, which reduced the problem of real-time s. ex-post data present in the GDP data.
J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138 121
USA
-10
-5
0
5
10
15
20
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
UK
-10
-5
0
5
10
15
20
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Swede n
-10
-5
0
5
10
15
20
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Canada
-10
-5
0
5
10
15
20
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Australia
-10
-5
0
5
10
15
20
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Note: The figure presents the evolut ion of the IMF stress index over time. Higher numbers indicate more stress (see Cardarelli et al., 2011).
Fig. 1. IMF financial stress indicator. Note: The figure presents the evolution of the IMF stress index over time. Higher numbers indicate more stress (see Cardarelli et al., 2
(
c w t t
011).
(12-month rolling beta, which is a measure of the correlation of banking stock returns to total returns in line with the CAPM).
(ii) Securities-market-related sub-index components: corporate bond spread (the difference between corporate bonds and long-term government bond yields), stock-market returns
(monthly returns multiplied by −1), time-varying stock-return volatility from the GARCH(1, 1) model.
iii) Foreign-exchange-related sub-index: the time-varying volatil- ity of monthly changes in NEER, from the GARCH (1, 1) model.
v 8 o i
We examined various alternative methods of aggregating the omponents – simple sum, variance-equal weighting, and PCA eighting – but failed to uncover any systematic differences among
hese in terms of the values of the overall index and consecutively in he empirical results. Cardarelli et al. (2011) confirm that extreme
alues of this indicator correctly identify almost all (approximately 0–90%) of the financial crises (including banking, currency, and ther crises, along with stock and house-price boom and busts) dentified in previous studies.
1 ncial
a f o n 2 d s t l i p t t H o v d t s a
3
a w n
r
w r t u c o
a d p e s
r
w i p a p p a p b o m v i
r
i ( m
c s 2 o p t t o a m s a
s s
r
W r m x i m e f s t i t a s b o t 6 t t
f t t t alternative methods for modeling structural changes in monetary- policy rules that occur on an unknown date: (i) regime-switching models, in particular state-dependent Markov switching models
12 More precisely, i equals 6 when we use monthly data and 2 for quarterly data. Although the targeting horizon of central banks is usually somewhat longer (4–8 quarters), as in the other papers in this stream of literature, we prefer to proxy inflation expectations by inflation in t + 2 quarters for the following reasons. First, the endogeneity correction requires a strong correlation between the endogenous regressor and its instruments. Second, the prediction error logically increases at longer horizons. Most importantly, the choice of i is in line with the theory. Batini and Nelson (2001) show that i = 2 in their baseline model of an optimal policy hori-
22 J. Baxa et al. / Journal of Fina
The use of a composite index has a number of benefits. First, it pproximates the evolution of financial stress caused by different actors and thus is not limited to one specific type of instability. Sec- nd, the inclusion of additional variables in the stress index does ot affect the evolution of the indicator markedly (Cardarelli et al., 011). Third, the composition of the indicator allows for breaking own the reactions of the central bank with respect to different tress subcomponents. Nevertheless, one has to be cautious about he interpretation. The composite indicator might suggest a mis- eading interpretation as long as the stress is caused by variables not ncluded in the FSI but rather highly correlated with some subcom- onent. An example is the case of Sweden during the ERM crisis. At he time of the crisis, Sweden maintained a fixed exchange rate, and he Riksbank sharply increased interest rates to sustain the parity. owever, this is not captured by the exchange-rate subcomponent f the FSI, which measures exchange-rate volatility, because the olatility was actually close to zero. A closer examination of the ata shows that this period of stress is captured by the inverted erm structure; hence, it is incorrectly attributed to bank stress. A imilar pattern can be observed for the UK, where the FSI increases fter the announcement of withdrawal from the ERM.
.2. The empirical model
Following Clarida et al. (1998a,b), most empirical studies ssume that the central bank sets the nominal interest rate in line ith the state of the economy typically in a forward-looking man- er:
∗ t = r̄ + ˇ(E[�t+i|˝t] − �∗t+i) + �E[yt+j|˝t] (1) here r∗t denotes the targeted interest rate, r̄ is the policy neutral
ate,10 �t+i stands for the central bank forecast of the yearly infla- ion rate, i indicates periods ahead based on an information set ˝t sed for interest-rate decisions available at time t, and �∗
t+i is the entral bank’s inflation target.11 yt+j represents a measure of the utput gap.
Nevertheless, Eq. (1) was found to be too restrictive to provide reasonable description of actual interest-rate setting. Notably, it oes not account for interest-rate smoothing by central banks, in articular the practice whereby the central bank adjusts the inter- st rate sluggishly to the targeted value. This is tracked in empirical tudies by the simple partial-adjustment mechanism:
t = �rt−1 + (1 − �)r∗t (2) here � ∈ [0, 1] is the smoothing parameter. There is an ongo-
ng controversy as to whether this parameter represents genuine olicy inertia or reflects empirical problems related to omitted vari- bles, dynamics or shocks (see, e.g., Rudebusch, 2006). The linear olicy rule in Eq. (1) can be obtained as the optimal monetary- olicy rule in the LQ framework, where the central bank aims only t price stability and economic activity. Bauducco et al. (2008) ropose an NK model with a financial system where the central ank has privileged information (given its supervisory function) n the health of the financial sector. In such a setting, the com-
on policy rule represented by Eq. (1) will be augmented by
ariables representing the health of the financial sector. Follow- ng this contribution, we consider the forward-looking rule where
10 The policy-neutral rate is typically defined as the sum of the real equilibrium ate and expected inflation. 11 An explicit definition of an inflation target exists only for countries with an nflation-targeting (IT) regime. Most empirical studies assume, in line with Taylor 1993), that this target does not vary over time and can be omitted from the empirical
odel.
z t r o t t t i t M b l r
Stability 9 (2013) 117– 138
entral banks may respond to a comprehensive measure of financial tress rather than stress in a particular segment (Bulíř and Čihák, 008). In practice, the augmented rule can be of some interest to utsiders because inflation expected by the individual monetary- olicy committee members is unobservable to the public (even hough some central banks publish figures that may be very close to he unobserved expected inflation, such as staff inflation forecasts r inflation forecasts stemming from interactions between staff nd monetary-policy committee members). In such case, outsiders ay benefit from including additional indicators such as financial
tress in the policy rule to predict the central bank’s behavior more ccurately.
Therefore, we substitute Eq. (2) into Eq. (1), eliminate unob- erved forecast variables and include measures of the financial tress described above, which results in Eq. (3):
t = (1 − �)[ ̨ + ˇ(�t+i − �∗t+i) + �yt+j] + �rt−1 + ıxt+k + εt (3) hile in Eq. (1) the term ̨ coincides with the policy-neutral rate
¯ , its interpretation is not straightforward once the model is aug- ented by additional variables. Note that the financial stress index
t+k does not appear within the square brackets. This is because t is typically not included in the loss function of central banks’
onetary policy but it is rather a factor such as the lagged inter- st rate, i.e., it may explain why the actual interest rate rt deviates rom the target. Moreover, by placing it in the regression at the ame level as a lagged interest rate, we can directly test whether his variable representing ad hoc policy decisions decreases the nterest-rate inertia �, as suggested by Mishkin (2009). At the same ime, the response on the coefficient ı can increase, as central banks re more likely to react to financial stress when stress is high. Con- equently, it is possible that � and ı move in opposite directions ecause the central bank either smoothes the interest-rate changes r adjusts the rates in the face of financial stress. In the latter case, he response is likely to be quick and substantial. We set i equal to , j equal to 0 and k equal to −1.12 Consequently, the disturbance erm εt is a combination of forecast errors and is thus orthogonal o all information available at time t (˝t).
The empirical studies on monetary-policy rules have moved rom using time-invariant estimates (Clarida et al., 1998a,b) hrough sub-sample analysis (Taylor, 1999; Clarida et al., 1998a,b) oward more complex methods that allow an assessment of he evolution of the conduct of monetary policy. There are two
on. However, alternative specifications of their model show some sensitivity in erms of what is the optimal i. Nevertheless, employing different i’s for regression esults left the results in most cases unchanged, to a large extent. In the case of the utput gap, we instead assume a backward-looking reaction. The reason is that in he absence of real-time data, we have to rely on the output-gap construction by sta- istical methods such as HP filter. It is arguable that aside from the prediction error, here is also a construction error that might be magnified if an unobserved forecast s substituted by the output-gap estimate for future periods. Finally, we assume hat central bankers’ response (if any) to financial stress is rather immediate (see
ishkin, 2009). Therefore, we use one lag of the FSI and its subcomponents in the enchmark case. However, as a robustness check, we allow for different lags and
eads, allowing the central bankers’ response to financial stress to be preemptive ather than reactive.
ncial
( a b K B a a g i T s s (
m U b w u o a o n i f c c b i a a s K
e v e r p e r e f
r
˛
ˇ
�
ı
�
�
y
x
s c c e
T i t o p i ( c f a ( d � ϕ i ( s E r g i
r
A s fi “ a l s s
∑
w s t p s a w i
•
•
J. Baxa et al. / Journal of Fina
Valente, 2003; Assenmacher-Wesche, 2006; Sims and Zha, 2006) nd (ii) state-space models, where the changes are characterized y smooth transitions rather than abrupt switches (Boivin, 2006; im and Nelson, 2006; Trecroci and Vassalli, 2010). As argued in axa et al. (2010), we consider the second approach to be prefer- ble for the estimation of policy rules, given that it is more flexible nd allows for the incorporation of a simple correction of endo- eneity (Kim, 2006; Kim and Nelson, 2006), which is a major issue n forward-looking policy rules estimated from ex-post data.13
he state-space approach, or time-varying coefficient model, also eems suitable when one wants to evaluate the effect of factors uch as financial stress that can, for a limited length of time, alter rather than permanently change) monetary-policy conduct.
State-space models are commonly estimated by means of a aximum likelihood estimator via the Kalman filter or smoother. nfortunately, this approach has several limitations that can ecome problematic in applied work. First, the results are some- hat sensitive to the initial values of the parameters, which are sually unknown, especially in the case of variables whose impacts n the dependent variable are not permanent and whose sizes re unknown, which is the case for financial stress and its effect n interest rates. Second, the log likelihood function is highly on-linear, and in some cases optimization algorithms fail to min-
mize the negative of the log likelihood. In particular, it can either ail to calculate the Hessian matrix throughout the iteration pro- ess, or, when the likelihood function is approximated to facilitate omputations, the covariance matrix of observation vectors can ecome singular for the starting values provided. The alternative
s a moment-based estimator proposed by Schlicht (1981, 2005) nd Schlicht and Ludsteck (2006), which is employed in our paper nd briefly described below. This framework is sufficiently flexible uch that it incorporates the endogeneity correction proposed by im (2006).
Kim (2006) shows that the conventional time-varying param- ter model delivers inconsistent estimates when explanatory ariables are correlated with the disturbance term and proposes an stimator of the time-varying coefficient model with endogenous egressors. Endogeneity may arise not only in forward-looking olicy rules based on ex-post data (Kim and Nelson, 2006; Baxa t al., 2010) but also in the case of variables that have a two-sided elationship with monetary policy. Financial stress unquestionably nters this category. Following Kim (2006), we rewrite Eq. (3) as ollows:
t = (1 − �t)[˛t + ˇt(�t+i) + �tyt+j] + �trt−1 + ıtxt+k + εt (4)
t = ˛t−1 + ϑ1,t, ϑ1,t∼i.i.d. N(0, �2ϑ1 ) (5)
t = ˇt−1 + ϑ2,t, ϑ2,t∼i.i.d. N(0, �2ϑ2 ) (6)
t = �t−1 + ϑ3,t, ϑ3,t∼i.i.d. N(0, �2ϑ3 ) (7)
t = ıt−1 + ϑ4,t, ϑ4,t∼i.i.d. N(0, �2ϑ4 ) (8)
t = �t−1 + ϑ5,t, ϑ5,t∼i.i.d. N(0, �2ϑ5 ) (9)
t+i = Z′t−m� + �ϕϕt, ϕt∼i.i.d. N(0, 1) (10)
t+j = Z′t−m + � t, t∼i.i.d. N(0, 1) (11)
t+k = Z′t−mo + ���t, �t∼i.i.d. N(0, 1) (12)
13 The time-varying parameter model with specific treatment of endogeneity is till relevant when real-time data are used (Orphanides, 2001). The real-time fore- ast is not derived under the assumption that nominal interest rates will remain onstant within the forecasting horizon (Boivin, 2006) or in the case of measurement rror and heteroscedasticity (Kim et al., 2006).
•
c
u
Stability 9 (2013) 117– 138 123
he measurement Eq. (4) of the state-space representation s the monetary-policy rule. The transitions in Eqs. (5)–(9) describe he time-varying coefficients as a random-walk process with- ut drift.14 Eqs. (10)–(12) track the relationship between the otentially endogenous regressors (�t+i, yt+j, and xt+k) and their
nstruments, Zt. We use the following instruments: �t−1, �t−12 �t−4 for CAN and SWE), yt−1, yt−2, rt−1, the foreign interest rate for ountries other than the United States (the three-month EURIBOR or SWE and UK, and the US three-month interbank rate for CAN nd AUS). Unlike Kim (2006), we assume that the parameters in Eqs. 10)–(12) are time-invariant. The correlation between the stan- ardized residuals ϕt, t, and �t and the error term εt is �ϕ,ε, � ,ε, and �,ε, respectively (note that �ϕ, � , and �� are the standard errors of t, t, and �t, respectively). Consistent estimates of the coefficients
n Eq. (4) are obtained in two steps. In the first step, we estimate Eqs. 10)–(12) and save the standardized residuals ϕt, t, and �t. In the econd step, we estimate Eq. (13) along with Eqs. (5)–(9). Note that q. (13) now includes bias correction terms, i.e., the (standardized) esiduals from Eqs. (10)–(12), to address the aforementioned endo- eneity of the regressors. Consequently, the estimated parameters n Eq. (13) are consistent, as t is uncorrelated with the regressors.
t = (1 − �t)[˛t + ˇt�t+6 + �tyt−1] + �trt−1 + ıtxt−1 + �ϕ,ε�εϕt + � ,ε�ε t + ��,ε�ε�t + t, t∼N(0, (1 − �2ϕ,ε − �2v,ε − �2�,ε)�2ε,t)
(13)
s previously noted, instead of the standard framework for second- tep estimation, the maximum likelihood estimator via the Kalman lter (Kim, 2006), we use an alternative estimation framework, the varying coefficients” (VC) method (Schlicht, 1981, 2005; Schlicht nd Ludsteck, 2006). This method is a generalization of the ordinary east squares approach that, instead of minimizing the sum of the quares of the residuals
∑T t=1
2, uses minimization of the weighted um of the squares:
T
t=1 2 + �1
T∑
t=1 ϑ21 + �2
T∑
t=1 ϑ22 + · · · + �n
T∑
t=1 ϑ2n (14)
here the weights �i are the inverse variance ratios of the regres- ion residuals εt and the shocks in time-varying coefficients ϑt, hat is, �i = �2/�2i . This approach balances the fit of the model and arameter stability. Additionally, the time averages of the regres- ion coefficients, estimated by a weighted least squares estimator, re identical to their GLS estimates of the corresponding regression ith fixed coefficients, that is, (1/T)
∑T t=1ât = âGLS.15 The method
s useful in our case because:
it does not require knowledge of initial values even for non- stationary variables prior to the estimation procedure. Instead, both the variance ratios and the coefficients are estimated simul- taneously; the property of the estimator that the time averages of the esti- mated time-varying coefficients are equal to its time-invariant counterparts, permits easy interpretation of the results in relation to time-invariant results;
it coincides with the MLE estimator via the Kalman filter if the time series are sufficiently long and if the variance ratios are properly estimated.16 However, this method suffers from
14 Note that while a typical time-invariant regression assumes that at = at−1 , in this ase, it is assumed that E[at ] = at−1 . 15 See Schlicht and Ludsteck (2006) and Baxa et al. (2010) for more details. 16 The Kalman filter as implemented in common econometric packages typically ses the diffusion of priors for its initiation, but it still produces many corner
1 ncial
t t o p q b k i t i r t fi r e i W w i l a i
c fi f t r fi i i n c F s c o i o b s
s c t m u t M O c i t i
t c t
4
s o s o m a o
4
i s a a t s t g o r a t S s s a
i s c a f f ( o m r v c a ( T b
24 J. Baxa et al. / Journal of Fina
certain limitations of its own. In particular it requires that: (a) the time-varying coefficients are described as random walks, and (b) the shocks in time-varying coefficients ϑt are minimized (see Eq. (14)).
While this does not represent a major problem for the estima- ion of the coefficients of common variables such as inflation, where he monetary-policy response is permanent, it can lead to a loss f some information about ad hoc response factors in monetary olicy making that are considered by central bankers only infre- uently; however, once they are in place, the policy response can e substantial. The financial stress indicator xt+k seems to be this ind of factor. One way to address this problem is by estimation- ndependent calibration of the variance ratios in Eq. (14), such that he estimated coefficient is consistent with economic logic, i.e., it s mostly insignificant and can become significant (with no prior estriction on its sign) during periods of financial stress, i.e., when he financial stress indicator is different from zero. Therefore, we rst estimate Eq. (13) using the VC method and study whether the esulting coefficients in the FSI correspond to economic intuition, specially whether the coefficient is not constant or slowly mov- ng (the so-called pile-up problem, see Stock and Watson, 1998).
hen this problem occurs, we compare the results with models here k belongs to (−2, −1, 0, 1, 2) and calibrate the variance ratios
n Eq. (13) by the variance ratios estimated for the model with the argest variances in the FSI. This step was necessary for Australia nd Sweden. The Taylor-rule coefficients were compared with the nitial estimates and were consistent in both cases.17
The results of our empirical analysis should reveal whether entral banks adjusted their interest-rate policies in the face of nancial stress. However, the time-varying framework also allows
or inferring whether any response to financial stress led to the emporal dismissal of other targets, in particular the inflation ate. Therefore, we are mainly interested in the evolution of the nancial-stress coefficient ıt. We expect it to be mostly insignif-
cant or zero, given that episodes of financial stress are rather nfrequent, and even if they occur, the monetary authorities may ot always respond to them. Moreover, the size of the estimated oefficient does not have any obvious interpretation because the SI is a composite indicator normalized to have a zero mean. Con- equently, we define the stress effect as a product of the estimated oefficient ıt and the value of the IMF’s FSI xt+k. The interpretation f the stress effect is straightforward: it shows the magnitude of nterest-rate reactions to financial stress in percentage points or, in ther words, the deviation from the target interest rate, as implied y the macroeconomic variables, due to the response to financial
tress.
olutions and often does not achieve convergence. Schlicht and Ludsteck (2006) ompare the performance of the moment estimator and the Kalman smoother in erms of the mean squared error on simulated data, and they conclude that the
oment estimator outperforms the Kalman filter on small samples with a size of p to 100 observations. For comparison, we estimated Eq. (12) using the conven- ional Kalman filter in the GROCER software using the tvp function (Dubois and
ichaux, 2009). We parameterized the model by initial conditions taken from the LS estimates of the parameters on the full sample and the initial forecast error ovariance matrix set to 0. The matrix of the residuals of time-varying coefficients s assumed to be diagonal, as in the VC method. The results were very similar to hose obtained from the VC method when the estimated variances were the same n both methods. 17 Stock and Watson (1998) propose a medium-unbiased estimator for variance in he time-varying parameter model, but its application is straightforward only in the ase of one time-varying coefficient, and more importantly, it requires the variables o be stationary.
i a a s i
s a a
e w
e s p r
Stability 9 (2013) 117– 138
. Results
This section summarizes our results on the effect of financial tress on interest-rate setting. First, the results on the effect of the verall measure of financial stress on interest-rate setting are pre- ented. Second, the effect of specific components of financial stress n monetary policy is examined. Third, we briefly comment on the onetary-policy rule estimates that served as the input for the
ssessment of financial-stress effects. Finally, we perform a series f robustness checks.
.1. Financial-stress effect
Fig. 2 presents our results on the effect of financial stress on nterest-rate setting in all five countries (referred to as the financial- tress effect hereinafter).18 Although there is some heterogeneity cross countries, some global trends in the effect of financial stress re apparent. Whereas in good times, such as in the second half of he 1990s, financial stress has virtually no effect on interest-rate etting or is slightly positive,19 the reaction of monetary authori- ies to financial stress was highly negative during the 2008–2009 lobal financial crisis. While the previous evidence on the effect f financial stress on monetary policy is somewhat limited, our esults broadly confirm the time-invariant findings of Cecchetti nd Li (2008), who show that the US Fed adjusted interest rates to he procyclical impact of bank capital requirements in 1989–2000. imilarly, Belke and Klose (2010) estimate the Taylor rule on two ub-samples (before and during the 2008–2009 global financial cri- is) and find that the Fed reacted systematically not only to inflation nd the output gap, but also to asset prices, credit, and money.
The size of financial-stress effects on interest-rate setting dur- ng the recent financial crisis is somewhat heterogeneous, with the trongest reaction found for the UK. The results suggest that all entral banks except the Bank of England maintain policy rates at pproximately 50–100 basis points lower compared to the counter- actual policy of no reaction to financial stress. The size of this effect or the UK is assessed to be approximately three times stronger i.e., 250 basis points). This implies that approximately 50% of the verall policy-rate decrease during the recent financial crisis was otivated by financial-stability concerns in the UK (10%–30% in the
emaining sample countries), while the remaining half falls to unfa- orable developments in domestic economic activity. This finding omplements previous results suggesting that the BoE’s consider- tion of expected inflation over the last decade has been very low as found by Baxa et al., 2010, using the time-varying model and by aylor and Davradakis, 2006, in the context of the threshold model) y evidence that it further decreased during the current crisis. It
s also evident that the magnitude of the response is unusual for ll five central banks. However, the results for Australia, Canada, nd Sweden show a similar magnitude of response to financial tress during the recent financial crisis compared to that observed n previous periods of high financial stress.
Given that the 2008–2009 global crisis occurred at the end of our
ample (there is a peak in the stress indicator of five standard devi- tions that has not returned to normal values yet), we performed an dditional check to avoid possible end-point bias. In particular, we
18 Given that the magnitude of the financial-stress effect differs across countries, specially due to the high positive peak for Sweden and negative peak for the UK, e use different scales for different countries.
19 Note that the positive effect of financial stress on interest-rate setting is to some xtent a consequence of scaling the financial-stress indicator; its zero value corre- ponds to the long-run average stress. Hence, we do not pay much attention to ositive values of stress unless caused by a temporarily positive and significant egression coefficient associated with the FSI.
J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138 125
USA
-0.6
-0.5
-0.4
-0.3
-0.2
-0.1
0
0.1
0.2
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
UK
-2.5
-2
-1.5
-1
-0.5
0
0.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Sweden
-2
-1
0
1
2
3
4
5
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Canada
-0.5 -0.4 -0.3 -0.2 -0.1
0 0.1 0.2 0.3 0.4 0.5 0.6
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Australia
-0,8
-0,6
-0,4
-0,2
0
0,2
0,4
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Notes: The figu re depicts the evolution of the financial-stress effect. The stress effect (y-axis) is coefficient estimated the of product the as defined the in indicator financial-stress the on
shows t he ma gnitude of the i nte rest -rate r eaction to financial stress in percentage points.
F ts the p ary-po s points
r 2 f r C q t
( t 1
ig. 2. The effect of financial stress on interest-rate setting. Notes: The figure depic roduct of the estimated coefficient on the financial-stress indicator in the monet hows the magnitude of the interest-rate reaction to financial stress in percentage
an our estimation excluding the observation from the period of the 008–2009 crisis. These results were practically indistinguishable rom the full sample estimation. With regard to the effect of the cur-
ent crisis, the largest uncertainty is associated with the results for anada, for which the shortest data sample – ending in the fourth uarter of 2008 – was available. When the possibility of a preemp- ive reaction of the central bank to financial stress is considered
t t
i
evolution of the financial-stress effect. The stress effect (y-axis) is defined as the licy rule and the value of the IMF financial-stress indicator (ıx). The stress effect .
see the robustness checks below), the effect of financial stress in he current crisis is estimated for Canada at somewhere between % and 2% (see Appendix 3). These additional results suggest that
he response of the Bank of Canada in the benchmark model is likely o be underestimated.
The question of which components of financial stress influence nterest-rate setting is addressed in Fig. 3. In this case, we estimate
126 J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138
USA
-0.6
-0.5
-0.4
-0.3
-0.2
-0.1
0
0.1
0.2
0.3 19
81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Ban k stres s Stoc k market stress Exchan ge rate stres s
UK
-2
-1.5
-1
-0.5
0
0.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Ban k stres s Stock market stres s Exchan ge rate stres s
Sweden
-3 -2
-1 0 1
2 3 4
5 6
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Bank stress Stock mar ket stre ss Exchange rate stress ERM crisis
Canada
-1.5
-1
-0.5
0
0.5
1
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Ban k stres s Stock market stres s Exchan ge rate stres s
Australia
-2
-1,5
-1
-0,5
0
0,5
1
1,5
2
2,5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Bank stress Stock market stress Exchang e rate stress
Notes: The f igure depicts the evolution of the components of the financial-stress effect, namely, the bank-s tress effect, the exchange- rate st ress effect, and the stock-market stress effect. The
defined is (y-axis) effect stress given the on coefficient estimated the of product the as component of the financ ial-stress indicator in the monetary-policy rule and the value of the
Fig. 3. The effect of financial stress components on interest-rate setting: bank stress, exchange-rate stress, and stock-market stress. Notes: The figure depicts the evolution o xchan d nanc c gnitu
t e e e i b
c e
f the components of the financial-stress effect, namely, the bank-stress effect, the e efined as the product of the estimated coefficient on the given component of the fi omponent of the IMF financial-stress indicator (ıx). The stress effect shows the ma
he model using each FSI subcomponent separately (the bank stress ffect, the exchange-rate stress effect, and the stock-market stress
ffect) instead of the overall FSI and report the financial-stress ffect attributable to each subcomponent. Some heterogene- ty across countries is again apparent, although it seems that ank stress and stock-market stress dominated central bankers’
C
i m
ge-rate stress effect, and the stock-market stress effect. The stress effect (y-axis) is ial-stress indicator in the monetary-policy rule and the value of the corresponding de of the interest-rate reaction to financial stress in percentage points.
onsiderations in less open economies. On the other hand, xchange-rate stress matters in more open economies such as
anada and Sweden.
Specifically, the US Fed seemed to be worried about financial nstability, especially during the 1980s. We can observe that the
ain concern in the early 1980s was banking stress, which is
ncial
a w m r
t s t e t t 2 i e u a t o t o i p i u h w l i i r o k p
e F fi 2 c o s t a s t
R u R t l e a a
t u m o l r i p i
d s i
i t h e t t c
s n o c c t
t m i e
4
t e p F v u s
c p d t T c l 2 b t d b w
i
J. Baxa et al. / Journal of Fina
rguably related to the Savings and Loans crisis. Another concern as that of stock-market stress, in particular during the stock- arket crash of 1987, when interest rates were 30 b.p. lower with
espect to the benchmark case. The Bank of England was, in general, much more perceptive
o financial stress. We find its response mainly to stock-market tress again, notably, in 1987. Interestingly, we find little response o exchange-rate stress, not even during the 1992 ERM crisis. Nev- rtheless, it has to be emphasized that the interest-rate reaction to his speculative attack was subdued in comparison to, for example, he Riksbank (Buiter et al., 1998). The base rate was increased by
p.p. to 12% on September 16, 1992. Despite a promise of further ncreases up to 15%, traders continued selling the pound. On the vening of the same day, the UK left the ERM with interest rates nchanged; on the following day, the base rate decreased to 10.5%; nd at the end of September, the base rate was 9%, lower than at he beginning of the month. Therefore, despite huge open market perations, the response of the interest rate was moderate, with he monthly interest-rate average practically unaffected. Hence, ur framework does not detect any effect of financial stress on the nterest rate during the ERM crisis. Since the devaluation of the ound sterling in September 1992, the effect of financial stress on
nterest-rate setting approaches zero from originally negative val- es. Aside from this, the response of the Bank of England to inflation as decreased. From this perspective, it seems the pound sterling’s ithdrawal from the ERM allowed for both a more rule-based and
ess restrictive monetary policy. With respect to the banking crisis n the late 2000s, the Bank of England provided liquidity support n its earlier stage in 2007 with the fall of Northern Rock. Policy ates remained constant until late 2008, despite the bankruptcy f Lehman Brothers in the US in September 2008. The reason for eeping policy rates constant was related to concerns regarding otential inflationary pressures from rising oil and food prices.
The interest-rate effect of the banking crisis in Sweden in the arly 1990s is estimated to be slightly over 1% in absolute terms (see ig. 2). The crisis began in September 1990, when the non-banking nancial institution Nyckeln unexpectedly collapsed (Jennergren, 002). The Riksbank did not decrease interest rates sharply because oincidental international factors, in particular the reunification f Germany, forced interest rates upwards. Despite facing reces- ion, the government attempted to defend the peg of the krona o ECU and decided to prevent the spread of the banking crisis by nnouncing a blanket guarantee for the liabilities of the banking ector (Jonung, 2009). Hence, interest-rate cuts were not a primary ool chosen for resolution of the crisis.
In comparison to the United Kingdom, the reaction of the iksbank to the ERM crisis was different. First, after a series of spec- lative attacks on the Swedish krona in mid-September 1992, the iksbank still attempted to maintain the fixed exchange rate, and he marginal interest rate jumped up 500% to offset the outflow of iquidity and other speculative attacks (see the large positive stress
ffect on the interest rate in 1992 in Fig. 2). However, not even such n increase was sufficient, and the fixed exchange rate had to be bandoned later, in November.20
20 For Sweden, we add a dummy variable for the third quarter of 1992 (ERM crisis) o Eq. (13). At this time, the Swedish central bank forced short-term interest rates pward in an effort to keep the krona within the ERM. From the perspective of our odel, it was a case of a strong positive reaction to the actual stress that lasted
nly one period. When this dummy variable was not included, the model with a agged value of the FSI was unable to show any link between stress and interest ates, and the estimates of other coefficients were inconsistent with economic intu- tion. Clearly, since we use data at monthly and quarterly frequency, this limits the ossibility to detect and properly analyze day-to-day dynamics of some short-term
nstability events.
f h p a c o i l t e l R i o
Stability 9 (2013) 117– 138 127
The Reserve Bank of Australia significantly loosened its policy uring the 1980s. This can be attributed to stress in the banking ector with the exception of the reaction to the stock-market crash n 1987 (see Fig. 3).
The exchange rate as well as bank stress seems to matter for nterest-rate considerations at the Bank of Canada. Interestingly, he results suggest that the Bank of Canada often responded to igher exchange-rate stress by monetary tightening. A possible xplanation for this finding might be that given the openness of he Canadian economy, its central bank tightened the policy when he currency stabilized at the level that the monetary authority onsidered to be undervalued.
We would like to highlight a comparison of Figs. 2 and 3. First, it hould be noted that a positive response to one stress subcompo- ent may cancel out in the face of a negative response to another ne, making the response to the overall stress negligible (as in the ase of Canada). Second, the stress effects related to individual sub- omponents do not necessarily sum up to the stress effect related o the entire FSI.
Overall, the results suggest that the central bank tends to react o financial stress, and different components of financial stress
atter in different time periods. The effect of financial stress on nterest-rate setting is found to be virtually zero in good times and conomically sizable during periods of high financial stress.
.2. Monetary policy rule estimates
Given that our main interest lies in the interest-rate response o financial stress, we comment on the other monetary-policy rule stimates only briefly. The plot of the evolution of the estimated arameters over time for all countries is available in Appendix 1. irst of all, it should be noted that most coefficients do indeed ary over time, which is consistent with previous evidence and nderlines the fact that monetary-policy conduct has evolved sub- tantially in recent decades.
In general, the responses to inflation (ˇ) are positive, and the oefficient is often above one, consistent with the Taylor princi- le. Nevertheless, we find that in the last decade the coefficient ecreased somewhat, and during the recent financial crisis it even urned slightly negative (in the US and UK; more on this below). he decrease of the inflation response during the last decade is typi- ally attributed to well-anchored inflation expectations as well as a ow-inflation environment (Sekine and Teranishi, 2008; Baxa et al., 010). The finding of negative ˇ during the recent crisis is likely to e related to the fact that central banks were decreasing policy rates o historical lows in the face of exceptionally high financial stress, espite inflation expectations being largely unchanged, rather than eing an indication that policy rates were systematically decreased hen inflation expectations increased.
For the United States, our results show that the response to nflation was highest in the early 1980s, and except for the period ollowing the recession of 1990–1991 the estimated coefficient is igher or very close to one. This value is slightly lower in com- arison to Kim and Nelson (2006), who found the response to be round 1.5 and almost invariant since 1981. Given the size of the onfidence intervals, it is, however, difficult to determine whether ur results differ significantly. Kim and Nelson (2006) estimate the nterest-rate smoothing coefficient to be higher than 0.8, i.e., in ine with what time-invariant estimates of monetary-policy rules ypically suggest (see, for example, Clarida et al., 1998a,b). Our stimates indicate that the interest-rate smoothing is somewhat
ower (0.5–0.6). This finding is in line with the recent critique by udebusch (2006), who argues that the practical unpredictability of
nterest-rate changes over a few quarters suggests that the degree f interest-rate smoothing is rather low. Interestingly, we find that
128 J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138
Response to inflation ( )
-3
-2
-1
0
1
2
3
4
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Response to output gap ( )
-0.1
0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Interest rate smoothin g ( )
0 0.1 0.2 0.3 0.4 0.5 0.6 0.7 0.8 0.9
1
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Response to financial stress ( )
-0.12
-0.1
-0.08
-0.06
-0.04
-0.02
0
0.02
0.04
0.06
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Note: The estima ted coefficie nts o f the time -varying monetary policy rule are depicted with a
F ts of t
t i ( t r m t ( t r p w t t a f s a
f a w u c R d
t f
p t t e e c t w b d t c
s l s l a t f t a a
95% confidence interval.
ig. A1.1. Time-varying monetary policy rules: USA. Note: The estimated coefficien
he response to inflation decreases substantially after the terror- st attacks on September 11, 2001. This complies with Greenspan 2007), who argued in that case that the Fed was concerned about he US economy spiraling downward into recession after the ter- orist attacks. Later, Greenspan himself acknowledged that the onetary policy was somewhat loose, but ex ante optimal, given
he increased uncertainty after the attacks. In a similar vein, Taylor 2010) compares the actual values of the federal funds rate and he counterfactual values predicted by the (time-invariant) Taylor ule, finding that in 2002–2005 interest rates were too low com- ared to predictions and this deviation from a rules-based policy as “larger than in any period since the unstable decade before
he Great Moderation” (p. 167). Negative estimates of the response o inflation in this particular period are reported also by Trecroci nd Vassalli (2010). The response to the output gap is significant or nearly the whole sample, although the values close to 0.2 are omewhat lower than in Kim–Nelson (2007), but similar to Trecroci nd Vassalli (2010).
The results for countries that currently have an explicit target or inflation share several features. The interest-rate smoothing is gain found to be lower in comparison to time-invariant estimates, ith midpoints around 0.5. The exception is Canada, where the val- es fluctuate around zero and are insignificant. Moreover, for some
entral banks, such as the RBA and the BoE in 2010 or the Sveriges iksbank in late 1980, we find that central banks are less inertial uring crises.21 Second, the response of interest rates to inflation is
21 Indeed, the correlation coefficient of the estimated time-varying coefficient of he lagged interest rate � and the financial-stress index ı is −0.79 for Australia, 0.21 or Canada, −0.20 for Sweden, −0.68 for the UK, and 0.60 for the US.
t t p
4
a
he time-varying monetary policy rule are depicted with a 95% confidence interval.
articularly strong during the periods when central bankers want o break a record of high inflation, such as in the UK or Australia at he beginning of the 1980s, and is less aggressive in a low-inflation nvironment with subdued shocks and well-anchored inflation xpectations (Kuttner and Posen, 1999). In this respect, our results onfirm the findings of Taylor and Davradakis (2006), who argue hat the response of the Bank of England to inflation is insignificant hen the inflation rate is close to its target. Third, some central
anks (Australia and Canada) are also found to react to output-gap evelopments, with the parameter estimated to be slightly posi- ive on average, whereas the parameter is insignificant with wide onfidence intervals in Sweden and the United Kingdom.
The results show that the interest-rate response to financial tress is insignificant most of the time, at the 95% significance evel. This is in line with our expectations, i.e., that the coefficients hould be insignificant in periods when stress is low. Neverthe- ess, the coefficient on financial stress is statistically significant t the 95% level during the recent financial crises for most coun- ries. The importance of financial stress for interest-rate setting is urther confirmed using the GMM estimation, which shows that he financial-stress index is significant, in fact, in all countries. In ddition, when the one-standard-deviation quantile is taken into ccount instead of the more usual two-standard-deviation quan- ile, the periods when we can identify any interest-rate response o financial stress become more evident. We present a list of these eriods in Table A5.2.
.3. Robustness checks
In terms of the financial-stress effect estimates, we perform battery of robustness checks. First, following the argument put
J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138 129
Response to inflation ( )
-1.5
-1
-0.5
0
0.5
1
1.5
2
2.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Response to output gap ( )
-0.3 -0.25 -0.2
-0.15 -0.1
-0.05 0
0.05 0.1
0.15 0.2
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Interest rate smoothin g ( )
-0.1
0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
0.8
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Response to financial stress ( )
-0.25 -0.2
-0.15 -0.1
-0.05 0
0.05 0.1
0.15 0.2
0.25
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Note: The estima ted coef ficients o f the time -varying monetary policy rule are depicted with a 95% confidence interval.
Fig. A1.2. Time-varying monetary policy rules: UK. Note: The estimated coefficients of the time-varying monetary policy rule are depicted with a 95% confidence interval.
Response to inflation ( Response to output gap () )
Interest rate smoothin g ( Response to financial stress () )
Note: The estima ted coefficie nts o f the time -varying monetary policy rule are depicted with a 95% confidence interval.
0
0.5
1
1.5
2
2.5
3
3.5
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
-0.6
-0.4
-0.2
0
0.2
0.4
0.6
0.8
1
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
-0.4
-0.2
0
0.2
0.4
0.6
0.8
1
1.2
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
-0.8
-0.6
-0.4
-0.2
0
0.2
0.4
0.6
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
Fig. A1.3. Time-varying monetary policy rules: Sweden. Note: The estimated coefficients of the time-varying monetary policy rule are depicted with a 95% confidence interval.
130 J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138
Response to inflation (β)
0
0.5
1
1.5
2
2.5
3
3.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Response to output gap (γ)
Interest rate smoothin g ( ρ)
-0.2
0
0.2
0.4
0.6
0.8
1
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Response to financial stress (δ)
Note: The estima ted coefficie nts o f the time -varying monetary policy rule are depicted with a 95% confidence interval.
-0.2
0
0.2
0.4
0.6
0.8
1
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
-0.12
-0.1
-0.08
-0.06
-0.04
-0.02
0
0.02
0.04
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Fig. A1.4. Time-varying monetary policy rules: Australia. Note: The estimated coefficients of the time-varying monetary policy rule are depicted with a 95% confidence interval.
Response to inflation (β)
0
0.2
0.4
0.6
0.8
1
1.2
1.4
1.6
1.8
2
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
Response to output gap (γ)
0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
Interest rate smoothin g ( ρ)
-1.2
-1
-0.8
-0.6
-0.4
-0.2
0
0.2
0.4
0.6
0.8
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
Response to financial stress (δ)
-0.4
-0.3
-0.2
-0.1
0
0.1
0.2
0.3
0.4
0.5
0.6
19 81
19 84
19 87
19 90
19 93
19 96
19 99
20 02
20 05
20 08
Note: The estimated coef ficients o f the time -varying monetary policy rule are depicted with a 95% confidence interval.
Fig. A1.5. Time-varying monetary policy rules: Canada. Note: The estimated coefficients of the time-varying monetary policy rule are depicted with a 95% confidence interval.
J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138 131
USA
-2.5
-2
-1.5
-1
-0.5
0
0.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
UK
-2.5
-2
-1.5
-1
-0.5
0
0.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Sweden
-0.8
-0.6
-0.4
-0.2
0
0.2
0.4
0.6
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Canada
-0.6
-0.5
-0.4
-0.3
-0.2
-0.1
0
0.1
0.2
0.3
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Australia
-0.7
-0.6
-0.5
-0.4
-0.3
-0.2
-0.1
0
0.1
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Notes: The figu re depicts the evolution of the financial-stress effect. The stress effect (y-axis) is coefficient estimated the of product the as defined the in indicator financial-stress the on
monetary-po licy rule and the va lue of the IMF financial-stress indicator ( x). The stress effect shows t he ma gnitude of the i nte rest -rate r eaction to financial stress in percentage points.
Fig. A2.1. The effect of financial stress on interest-rate setting. Notes: The figure depicts the evolution of the financial-stress effect. The stress effect (y-axis) is defined as t etary- s points
f b u a a t b
e a c
he product of the estimated coefficient on the financial-stress indicator in the mon hows the magnitude of the interest-rate reaction to financial stress in percentage
orward above that the interbank rate may occasionally provide a etter signal of monetary-policy intentions than the policy rate, we se interbank interest rates as a dependent variable. These results
re reported in Figs. A2.1 and A2.2. We can observe that the over- ll stress effect on the interbank rate was larger for the US during he current crisis, where it explains 2% of the decrease of the inter- ank interest rate. For Sweden, we found a strong positive effect of
r v
t
policy rule and the value of the IMF financial-stress indicator (ıx). The stress effect .
xchange rate volatility in the late 1980s; this might be linked to the im of the central bank to keep the exchange rate fixed. In other ases, there is no substantial difference between the benchmark
esults and the results obtained using this alternative dependent ariable.
Second, in the benchmark model and all of the results reported hus far, we use the first lag of the FSI in the policy-rule estimation.
132 J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138
USA
-2
-1.5
-1
-0.5
0
0.5
1 19
81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Ban k stres s Stoc k market stress Exchan ge rate stres s
UK
-1.6 -1.4 -1.2
-1 -0.8 -0.6 -0.4 -0.2
0 0.2 0.4
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Ban k stres s Stock market stres s Exchan ge rate stres s
Swede n
-1.5
-1
-0.5
0
0.5
1
1.5
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Ban k stres s Stoc k market stress Exchan ge rate stres s
Canada
-1.5
-1
-0.5
0
0.5
1
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Ban k stres s Stock market stres s Exchan ge rate stres s
Australia
-0.25
-0.2
-0.15
-0.1
-0.05
0
0.05
0.1
0.15
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Ban k stres s Stock market stres s Exchan ge rate stres s
Notes: The f igure depicts the evolution of the components of the financial-stress effect, namely, the bank stress effect, the exchange-rate stress effect, and the stock-market stress effect. The
defined is (y-axis) effect stress given the on coefficient estimated the of product the as component of the financ ial-stress indicator in the monetary-policy rule and the value of the corresponding component of the IMF financial-stress indicator ( x). The stress effect shows the
to reaction interest-rate the of magnitude in stress financial points.percentage
Fig. A2.2. The effect of financial stress components on interest-rate setting: bank stress, exchange-rate stress and stock-market stress. Notes: The figure depicts the evolution of the components of the financial-stress effect, namely, the bank stress effect, the exchange-rate stress effect, and the stock-market stress effect. The stress effect (y-axis) is d nanc c gnitu
W o a t
efined as the product of the estimated coefficient on the given component of the fi omponent of the IMF financial-stress indicator (ıx). The stress effect shows the ma
e motivate this choice by the use of monthly data, the frequency f monetary-policy meetings of most central-bank boards, and the ssumption that policy actions are likely to be implemented in a imely fashion. In addition, we employ different lags and leads, in
t r a n
ial-stress indicator in the monetary-policy rule and the value of the corresponding de of the interest-rate reaction to financial stress in percentage points.
he latter case allowing the policy to be preemptive rather than eactive. In this case, we use the future realized value of the FSI s a proxy for the central bank’s expectation (in a similar man- er as to how it is routinely executed for inflation expectations)
J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138 133
USA
-2,5
-2,0
-1,5
-1,0
-0,5
0,0
0,5
1,0
1984 1988 1992 1996 2000 2004 2008
t-2 t-1 t t+1 t+2
United Ki ngd om
-2,5
-2,0
-1,5
-1,0
-0,5
0,0
0,5
1,0
1984 1988 1992 1996 2000 2004 2008
t-2 t-1 t t+1 t+2
Swede n
-2
-1
0
1
2
3
4
5
6
1988 1992 1996 2000 2004 2008
t-2 t-1 t t+1 t+2
Canad a
-2,5
-2
-1,5
-1
-0,5
0
0,5
1
1,5
1984 1988 1992 1996 2000 2004 2008
t-2 t-1 t t+1 t+2
Australia
-2,5
-2
-1,5
-1
-0,5
0
0,5
1
1984 1988 1992 1996 2000 2004 2008
t-2 t-1 t t+1 t+2
1 vs.
a F b s t p u b fi e
l c i a a v r o b i
f
t s
e u i o i w c s t e a o n p fi
Fig. A3.1. The effect of financial stress (t −
nd, consequently, treat the FSI as an endogenous variable (see ig. A3.1 for the results). To obtain comparable results, we cali- rate the variance ratios with the same values as in the baseline pecification. Although we find rather mixed evidence on preemp- ive policy actions, which may also be related to the inadequacy of roxying the expected values of financial stress by the actual val- es of the financial-stress indicator as well as the fact that a central ank might not react to the stress preemptively, the reaction to nancial stress in the current crisis is strongly negative for both xpected and observed stress.
Third, we further break down the FSI sub-indices to each under- ying variable to evaluate their individual contributions.22 The orresponding stress effects appear in Figs. A4.1 and A4.2. Break- ng down stock-market-related stress, we find that the US Fed nd the BoC react to the corporate bond spread, whereas the BoE nd Sveriges Riksbank are more concerned with stock returns and olatility. While the RBA seems to be concerned with both corpo- ate bond spreads and stock-market volatility in the 1980s, the role
f stock-related stress had substantially decreased by then. As far as ank-related stress is concerned, the TED spread plays a major role
n all countries apart from the UK, where the largest proportion of
22 This applies only to the banking and stock-market subcomponents because the oreign-exchange subcomponent is represented by a single variable.
t e
5
i
t − 2, t, t + 1, t + 2) on interest-rate setting.
he effect on the interest rate can be attributed to an inverted term tructure.
Fourth, because the verifications related to comparing our conometric framework to obvious alternatives such as, first, the se of a maximum likelihood estimator via the Kalman filter
nstead of the moment-based time-varying coefficient framework f Schlicht and, second, the use of a Markov switching model nstead of a state-space model, were provided in Baxa et al. (2010),
e estimate simple time-invariant monetary-policy rules for each ountry by the generalized method of moments, including various ubsamples. This simple evidence reaffirms that the analyzed cen- ral banks seem to pay attention to overall financial stress in the conomy. The FSI is statistically significant, with a negative sign nd a magnitude of between 0.05 and 0.20 for all countries. On the ther hand, the coefficients of its subcomponents often are not sig- ificant, and the exchange-rate subcomponent in some cases has a ositive sign. These results, which are available upon request, con- rm that to understand the interest-rate adjustment in response o financial stress, one should rely on a model allowing for a differ- ntial response across time.
. Concluding remarks
The 2008–2009 global financial crisis generated significant nterest in exploring the interactions between monetary policy and
134 J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138
UKUSA
CanadaSweden
Australia
-0.5
-0.4
-0.3
-0.2
-0.1
0
0.1
0.2
0.3
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Bank ing beta TE D spread Inverted term spread
-4
-3
-2
-1
0
1
2
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Bank ing beta TE D spread Inverted term spread
-1.5
-1
-0.5
0
0.5
1
1.5
2
2.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Bank ing beta TE D spread Inverted term spread
-1.5
-1
-0.5
0
0.5
1
1.5 19
81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Bank ing beta TE D spread Inverted term spread
-1.5
-1
-0.5
0
0.5
1
1.5
2
2.5
19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Bank ing beta TE D spread Inverted term spread
k stre
fi m c o t o d fi F c e
u
m a n e f b o a t
Fig. A4.1. The effect of ban
nancial stability. This paper aimed to examine in a systematic anner whether and how the monetary policy of selected main
entral banks (the US Fed, the Bank of England, the Reserve Bank f Australia, the Bank of Canada, and Sveriges Riksbank) responded o episodes of financial stress over the last three decades. Instead f using individual alternative measures of financial stress in ifferent markets, we employed the comprehensive indicator of nancial stress recently developed by the International Monetary und, which tracks overall financial stress as well as its main sub-
omponents, in particular banking stress, stock-market stress and xchange-rate stress.
Unlike a few existing empirical contributions that aim to eval- ate the impact of financial-stability concerns on monetary policy
t t t m
ss on interest-rate setting.
aking, we adopt a more flexible methodology that not only llows for the response to financial stress (and other macroeco- omic variables) to change over time, but also addresses potential ndogeneity (Kim and Nelson, 2006). The main advantage of this ramework is that it not only enables testing of whether central anks responded to financial stress at all, but also detects the peri- ds and types of stress that were the most worrying for monetary uthorities. Our results indicate that central banks truly change heir policy stances in the face of financial stress, but the magni-
ude of such responses varies substantially over time. As expected, he impact of financial stress on interest-rate setting is essen- ially zero most of the time, when the levels of stress are very
oderate. However, most central banks loosen monetary policy
J. Baxa et al. / Journal of Financial Stability 9 (2013) 117– 138 135
UKUSA
CanadaSweden
Australia
-0.5 -0.4 -0.3 -0.2 -0.1
0 0.1 0.2 0.3 0.4 0.5 0.6
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Corpo rate spread Stock returns Stock volatili ty
-0.6 -0.5 -0.4 -0.3 -0.2 -0.1
0 0.1 0.2 0.3 0.4 0.5
19 81
19 83
19 86
19 89
19 92
19 95
19 98
20 01
20 04
20 07
Corpo rate spread Stock returns Stock volatili ty
-2
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-1
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1
19 81
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Corpo rate spread Stock returns Stock volatili ty
-2
-1.5
-1
-0.5
0
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19 81
19 83
19 84
19 87
19 89
19 91
19 93
19 95
19 97
19 99
20 01
20 03
20 05
20 07
20 09
Corpo rate spread Stock returns Stock volatili ty
-0.4
-0.3
-0.2
-0.1
0
0.1
0.2
0.3
19 81
19 83
19 84
19 87
19 89
19 91
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19 99
20 01
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Corpo rate spread Stock returns Stock volatili ty
arket
w c c t e o
a fi s e o g
p t s s o m t u U
Fig. A4.2. The effect of stock-m
hen the economy faces high financial stress. There is some cross- ountry and time heterogeneity when we examine central banks’ onsiderations of specific types of financial stress. While most cen- ral banks seem to respond to stock-market stress and bank stress, xchange-rate stress is found to drive the reaction of central banks nly in more open economies
Consistent with our expectations, the results indicate that a size- ble fraction of the monetary-policy easing during the 2008–2009 nancial crisis can be explained by a direct response to the financial
tress above what might be attributed to the decline in inflation xpectations and output below its potential. However, the size f the financial-stress effect differs by country. The result sug- ests that all central banks except the Bank of England kept their
e t l b
stress on interest-rate setting.
olicy rates at 50–100 basis points lower, on average, solely due o the financial stress present in the economy. Interestingly, the ize of this effect for the UK is assessed at about three times tronger (i.e., 250 basis points). This implies that about 50% of the verall policy-rate decrease during the recent financial crisis was otivated by financial-stability concerns in the UK (10%–30% in
he remaining sample countries), while the remaining half falls to nfavorable developments in domestic economic activity. For the S Fed, macroeconomic developments themselves (a low-inflation
nvironment and output substantially below its potential) explain he majority of the interest-rate policy decreases during the crisis, eaving any further response to financial stress to be constrained y zero interest rates.
1 ncial
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a i l a
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N 1 r ( B 2 i c A i
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36 J. Baxa et al. / Journal of Fina
Overall, our results point to the usefulness of augmenting he standard version of monetary-policy rules by some measure f financial conditions to obtain a better understanding of the nterest-rate-setting process, especially when financial markets are
nstable. The empirical results suggest that the central banks con- idered in this study altered the course of their monetary policy n the face of financial stress. The recent crisis seems truly to be
p s i
able A5.1 ime-invariant reaction functions, GMM estimates.
˛ ˇ �
United States 1 5.59 (1.42) 1.59 (0.99) 1.51 (0.53) 2 −9.42 (4.78) 0.45 (0.33) 0.94 (0.34) United Kingdom 1 3.93 (1.31) 0.37 (0.52) 1.51 (0.39) 2 7.68 (2.78) −0.89 (0.74) 2.77 (0.71) Sweden 1 −1.87 (0.86) 2.59 (0.46) −0.16 (0.22) 2 0.24 (0.53) 2.03 (0.39) −0.12 (0.16) Australia 1 0.04 (0.79) 2.06 (0.3) −0.02 (0.1) 2 2.2 (0.93) 1.84 (0.22) 0.19 (0.14)
Canada 1 −0.33 (1.23) 2.07 (0.96) 0.87 (0.30) 2 1.21 (1.23) 1.67 (0.87) 0.75 (0.28)
United States: 1981:1–1999:12 sample 1 1.82 (1.27) 1.43 (0.57) 1.48 (0.27) 1* −0.25 (0.77) 2.18 (0.42) 0.3 (0.06) United States: Clarida et al. (1998a,b) – 1982:10–1994:12 sample 2 −0.1 (1.54) 1.83 (0.45) 0.56 (0.16) otes: Numbers in (·) are standard errors. The samples are as follows: United 983:3M–2009:5M, Sweden 1984:2Q–20091Q, Canada 1981:1Q–2008:4Q. Model 1: rt t = (1 − �)( ̨ + ˇ�t+k + �yt ) + �rt−1 . k equals 6 for the USA, the UK and Australia, 2 for Swed the RM crisis) is included. The coefficient is significant at the 5% level, when the ratio of oth models are estimated using the GMM. The list of instruments follows. United States
without lags of FSI in a set of instruments. United Kingdom: lags of interest rate, outp nflation, output gap, US money market rate and FSI (1–6, 9, 12). Sweden: lags of interes risis. Canada: interest rate, inflation, output gap, U.S. money market rate, and FSI (1–4). dditionally, we show the results for the USA estimated on the subsample 1981–1999. Th
ndustrial production in a similar fashion as in Clarida et al. (1998a,b). Their results are pr
able A5.2 eriods with significant responses to financial stress.
1980s
United States 2SD 1SD 1982:M11–1992
United Kingdom 2SD 1987:M08–1989:M11 1SD 1987:M01–1993
Sweden 2SD 1SD
Australia 2SD 1987M:04–1988:M10 1SD 1983:M07–1993
Canada 2SD 1SD 1982:Q3–1984:Q1
Stability 9 (2013) 117– 138
n exceptional period, in the sense that the response to financial nstability was substantial and coincided in all the countries ana- yzed, which is evidently related to intentional policy coordination bsent in previous decades. However, we have also observed that
revious idiosyncratic episodes of financial distress were, at least in ome countries, followed by monetary-policy responses of similar, f not higher, magnitude.
� ı J-Statistics p-Value
0.97 (0.01) −0.014 (0.006) 24.9808 0.6289 0.94 (0.01) 15.0451 0.8207
0.97 (0.01) −0.018 (0.004) 15.0423 0.5212 0.98 (0.01) 11.4534 0.4905
0.84 (0.04) −0.135 (0.029) 24.9808 0.6289 0.76 (0.05) 15.0451 0.8207
0.95 (0.01) −0.038 (0.006) 21.5261 0.9731 0.89 (0.02) 15.2464 0.9830
0.89 (0.04) −0.089 (0.023) 10.6859 0.8284 0.86 (0.05) 9.4332 0.7395
0.95 (0.01) −0.015 (0.007) 20.1672 0.8583 0.87 (0.02) −0.043 (0.012) 19.8946 0.8683
0.97 (0.03) 10.9000 0.9980
States: 1981:1M–2009:6M, United Kingdom: 1981:1M–2009:3M, Australia: = (1 − �)( ̨ + ˇ�t+k + �yt ) + �rt−1 + ıxt−1 . Model 2 does not contain financial stress: en and 4 for Canada. For Sweden, a dummy variable for the third quarter of 1992
coefficient to standard error is greater than 1.96. : lags of interest rate, output gap, inflation, and financial stress (1–6, 9, 12), model ut gap, inflation, and EURIBOR 3M (1–6, 9, 12), FSI (1–3). Australia: interest rate, t rate, inflation, output gap, EURIBOR 3M, and FSI (1–4)+ the dummy for the ERM
e model denoted as 1* has the output gap derived from the quadratic trend of log ovided for comparison with ours.
1990s 2000s
2008:M03–2009:M03 :M09 2007:M05–2009:M06
2007:M09–2009:M03 :M01 2006:M03–2009:M03
1990:Q2–1992:Q2 2001:Q2–2002:Q3 1993:Q1 2009:Q1 1999:Q4–2000:Q2
2008:M09–2009:M03 :M10 2002:M10–2009:M05
1996:M06–1997:M05
1992:Q3–1995:Q4
ncial
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J. Baxa et al. / Journal of Fina
cknowledgments
We thank Aleš Bulíř, Sofia Bauducco, Øyvind Eitrheim, Dana ájková, Bernhard Herz, Ekkehart Schlicht, Miloslav Vošvrda, and
eminar participants at the 7th Norges Annual Monetary Policy onference, the 15th International Conference on Macroeconomic nalysis and International Finance (Rethymno, Greece), the Bank f England, the Czech National Bank, the Institute of Information heory and Automation (Academy of Sciences of the Czech Repub- ic), Universitat de Barcelona, Universitat de Girona, Universitat de es Illes Balears, and Universidad Computense de Madrid for helpful iscussions. The views expressed in this paper are not necessarily hose of the Czech National Bank. This research was supported by he Grant Agency of the Czech Republic, project no. P402/11/1487.
ppendix 1. Time-varying monetary policy rule estimates Figs. A1.1–A1.5)
ppendix 2. The results with the interbank rate as the ependent variable in the policy rule
ppendix 3. The results with different leads and lag of the SI
ppendix 4. The results with individual variables of bank tress and stock-market stress
ppendix 5. Significance of the financial stress index in the stimated Taylor rules (Tables A5.1 and A5.2)
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- Time-varying monetary-policy rules and financial stress: Does financial instability matter for monetary policy?
- 1 Introduction
- 2 Related literature
- 2.1 Monetary policy (rules) and financial instability – some theories
- 2.2 Monetary policy (rules) and financial instability – empirical evidence
- 2.3 Measures of financial stress
- 3 Data and empirical methodology
- 3.1 The dataset
- 3.2 The empirical model
- 4 Results
- 4.1 Financial-stress effect
- 4.2 Monetary policy rule estimates
- 4.3 Robustness checks
- 5 Concluding remarks
- Acknowledgments
- Appendix 1 Time-varying monetary policy rule estimates (Figs. A1.1–A1.5)
- Appendix 2 The results with the interbank rate as the dependent variable in the policy rule
- Appendix 3 The results with different leads and lag of the FSI
- Appendix 4 The results with individual variables of bank stress and stock-market stress
- Appendix 5 Significance of the financial stress index in the estimated Taylor rules (Tables A5.1 and A5.2)
- References