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Credit demand, credit supply, and economic activity

  • Nathan S. Balke and Zheng Zeng EMAIL logo
Published/Copyright: October 5, 2013

Abstract

In this paper, we attempt to identify the separate contributions of credit demand, supply of financial intermediation, and supply of funds to fluctuations in indicators of credit conditions and to fluctuations in economic activity. We estimate a common factor model in which the six factors correspond to supply of funds, financial intermediation, credit demand, aggregate uncertainty, real economic activity, and inflation. We use a simple model of financial intermediation to motivate restrictions on the factor loadings designed to identify supply of funds, uncertainty, credit demand, and financial intermediation factors. We find that the supply of funds and financial intermediation factors explain most of the variation in interest rates spreads, while the financial intermediation and credit demand factors typically contribute to most of the fluctuations in credit quantity variables. For credit indicators, the 2008–2009 financial crisis appears to be largely due to a decline in the financial intermediation. However, this decline in financial intermediation seems to have originated from output and uncertainty shocks, rather than shocks to financial intermediation itself.


Corresponding author: Zheng Zeng, Department of Economics, Bowling Green State University, Bowling Green, OH 43403, USA, Tel.: +(419) 372-8397, e-mail:

  1. 1

    Including two lags of the idiosyncratic factors and two lags on the common factors provides a relatively parsimonious yet flexible model to capture the dynamics between the observables and the unobserved factors. We experimented with other lag lengths and the results were fairly similar.

  2. 2

    We estimated the state equation with VARs of three and six lags respectively, and the results of these two specifications are similar. In this paper we only report the results of the model with three VAR lags as this VAR yielded slightly more precise estimates of the factors.

  3. 3

    We obtain very similar results when we impose the same sign restrictions on government securities’ factor loadings as on the commercial paper and Libor rates.

  4. 4

    The commercial paper/T-Bill spread has often been used as an indicator of credit conditions [see for example, Friedman and Kuttner (1992)]. Similarly, the financial conditions indices of Hakkio and Keeton (2009) and Hatzius et al. (2010) include yields on government securities among their indicators.

  5. 5

    The results are insensitive to the choice of alternative short-rates with which to calculate the spreads.

  6. 6

    Total net borrowings of household sectors and nonfinancial business are obtained from the Federal Reserve Statistical Release, Z.1, Flow of Funds Accounts, Table F.1 “Total Net Borrowing and Lending in Credit Markets” and are the sum of lines 3–6.

  7. 7

    Lown and Morgan (2004) and Asea and Blomberg (1996) found that the lending standard survey is informative in explaining variation in business loans and real economic activity.

  8. 8

    The series is calculated following Gilchrist, Sim and Zakrajsek (2009a) and Bloom, Floetotto and Jaimovich (2009).

  9. 9

    We do not include Federal Reserve Balance sheet variables in our set of indicators precisely because these variables move so dramatically over this period.

  10. 10

    To save space we present only a selected number of indicators. The historical decompositions for all of the other indicators are available upon request.

  11. 11

    We only report the C&I loans, net credit tightening standard survey, loan availability survey, commercial bank total loans, and total credit liabilities. The decompositions of other series are consistent with the results of the selected indicators, and are available upon request.

  12. 12

    Perhaps, this is not too surprising given the correlations between innovations in the factors were relatively small, with the exception of credit demand and supply of financial intermediation. Changing the order of credit demand and financial intermediation affects the impulse response analysis somewhat but had little effect on the historical decompositions.

  13. 13

    The responses of the rest of the indicators are all consistent with the ones of the representative indicators. They are not reported here but are available upon request.

  14. 14

    Note that we do not impose any sign restriction on the factor loadings of short-term interest rates or interest rate spreads with respect to the uncertainty factor.

  15. 15

    On the advice of an anonymous referee, we checked to see whether the results were sensitive to the inclusion of the 2008–2009 financial crisis in the sample. We estimated the model up the 2006 and then used the Kalman filter to decompose the observed time series into contribution of the underlying factors and structural shocks for the entire sample. Most of the results using the short sample to estimate the model are similar to those of the model estimated to the full sample. Where the results differ are in decomposition of short-term interest rates. In the short sample model, the credit demand factor plays a larger role in the decomposition of short-term interest rates than in the full sample model.

  16. 16

    Balke (2000) examines a threshold VAR where the threshold variable depends on credit conditions. In this case, credit conditions can have an effect independent of credit shocks by triggering a change in regime.

  17. 17

    In our model, the elements of matrices A, H, F, Q and R.

Many thanks to Nick Bloom and William Dunkelberg for supplying their data. We also thank Tim Fuerst, Kundan Kishore, and Peter VanderHart as well as seminar participants at the June 2010 Western Economic Association Meetings and the February 2011 Eastern Economic Association Meetings for helpful comments and suggestions. The views expressed in this paper are solely those of the authors and not those of the Federal Reserve Bank of Dallas or the Federal Reserve System.

Appendix A

A. Bayesian estimation

Kim and Nelson (1998) and Johannes and Polson (2003) provide detailed introductions to Bayesian Markov Chain Monte Carlo methods. The objective of the estimation is to find the posterior distribution of both the unknown parameters, Θ,17 and the unobservable state vector, S, given the observable indicators, Y. By sequentially sampling S(i) from posterior distribution P(S|Θ, Y) and Θ(i) from P(Θ|S, Y), the resulting sample distribution of (S(i), Θ(i)) converges to P(S, Θ|Y).

Define and The steps taken in the Gibbs Sampler are as follows:

  1. Taking the parameters of the state space model as given, draw a realization of the state vector conditional on the model’s parameters and the observed data. Because the state space model presented by equation (1) and (2) is linear and Gaussian, the distribution of ST given and that of St given St+1 and for t=T–1, T–2, …, 1 are also Gaussian:

    STN(STT, PTT),

    where

    We can take Kalman filter approach to obtain STT and PTT by filtering forward:

    Stt=Stt–1+Ptt–1H′(HPtt–1H′+R)–1ηtt–1,

    Ptt=Ptt–1Ptt–1H′(HPtt–1H′+R)–1HPtt–1;

    where ηtt–1=(YtAYt–1HStt–1) in our model is the new information that Yt can bring to forecasting St, and is weighted by the variance of the conditional forecast error (HPtt–1H′+R).

    We draw from the conditional distribution, and obtain and by sampling backwards:

    where is the new information updated by the state equation and equals to (St+1FStt) in our model, and is weighted by the variance (FPttF′+Q).

  2. Taking state vector and variance-covariance matrix Q as given, draw parameters of the state equation, i.e., the elements in F matrix. We can rewrite the state equation in matrix form as below:

    y=ρX+ν, ν∼N(0, Q);

    where X=(S0S1ST–1) and y=(S1S2ST).

    We employ a multivariate normal prior distribution for ρ given by

    where are known and I[s(ρ)] is an indicator function used to denote that roots of F(L) lie outside the unit circle. The posterior distribution for ρ is given by

    where

    We draw ρ from the posterior and discard the draws if the roots lie outside the stationary region.

  3. Taking the state vector and F matrix as given, draw elements in the variance-covariance matrix Q. We employ an Inverse-Wishart prior distribution W–1o, κo), where Ψo and κo are known. The posterior distribution is given by W–11, κ1) where

  4. Taking the state vector and the R matrix as given, draw parameters in the measurement equation, i.e., the elements in A and H matrices. The posterior distributions have similar forms as those in step 2 with the linear regressions given by the measurement equations. Draws of parameters which resulted in roots lying outside the stationary region or violated sign restrictions were discarded and another new draw was made.

    In order to help setting the scale of the factors, we set tight priors (around one) on the coefficients of the Fed Funds rate, Commercial and Industrial loan growth, and S&P 500 composite volatility to set the scales of our credit, and uncertainty factors, respectively. Also, we normalize the factor loadings of real GDP and GDP deflator to fix the scale of our output and inflation factors.

  5. Taking the state vector and the parameter vector A(L) and H(L) as given, draw variances in R matrix from the Inverse-Wishart posterior distribution similar as those in step 3 with linear regressions given by the measurement equations.

  6. Repeat steps 1–5. This is done for a burn-in buffer of 100,000 draws after which every tenth draw is used to form the posterior distribution consisting of total 10,000 draws.

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Published Online: 2013-10-05
Published in Print: 2013-01-01

©2013 by Walter de Gruyter Berlin Boston

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