Abstract
The paper models monetary policy in China using a hybrid McCallum–Taylor empirical reaction function. The feedback rule allows for reactions to inflation and output gaps, and to developments in a trade-weighted exchange rate gap measure. The investigation finds that monetary policy in China has, on average, accommodated inflationary developments. But exchange rate shocks do not significantly affect monetary policy behaviour, and there is no evidence of a structural break in the estimated reaction function at the end of the strict dollar peg in July 2005. The paper also runs an exercise incorporating survey-based inflation expectations into the policy reaction function and meets with some success.
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Notes
Liu and Zhang (2007) note that there have been persistent deviations from uncovered interest rate parity.
For a thorough description of China's monetary policy, see Geiger (2008); Evenett (2010) discusses China's exchange rate policy.
http://www.pbc.gov.cn/english/huobizhengce/objective.asp.
Although an industrial production series in levels is available in current prices, no deflator is published; hence our choice of year-on-year growth rates (in constant prices) for construction of the output gap. Moreover, during the reform period, Chinese economic cycles have been ‘growth cycles’, with slowdowns and upturns in growth rates but no fall in the levels series.
The data are from the China Monetary Policy Report, from 2001 onwards (various issues). The targets prior to 2001 were obtained from the website of the National People's Congress of China (only in Chinese, link available from the authors upon request).
For 1998, when both RPI and CPI targets were announced by the government, this procedure produces a CPI target equal to the officially announced target.
When the Schwarz information criterion is used, a unit root can be rejected at 1% level for monetary base as well. Detailed results are available from the authors upon request.
The adjusted Portmanteau test for autocorrelation yields a test statistic of 253.24 (p-value of 0.14), and the LM test for autocorrelation with 4 and 1 lags amounts to 76.11 (0.60) and 9.24 (0.90), respectively. The multivariate ARCH-LM test yields a test statistic of 510.00, with a p-value of 0.37.
The result is obtained by calculating the long-run impact, that is, adding up the lagged coefficients of the output gap.
Burdekin and Siklos (2008) find a procyclical response of monetary policy to movements in nominal GDP. However, they do not estimate policy reactions to movements in real output and inflation separately.
According to the International Monetary Fund (2003), both transitory and long-term supply shocks contributed to deflation in China in the late 1990s and early 2000s.
Dai (2006) reports that the PBoC would have adopted interest rates as the intermediate goal in 2004. Nevertheless, in 2009, intermediate targets for monetary aggregates and credit growth were announced by the PBoC. Furthermore, base money can be used as an instrument even with a change in the intermediate target by the monetary authority.
The results can be obtained from the authors upon request.
Restricting the coefficient on the exchange rate shock to zero is not supported by the data, judging by the test on over-identifying restrictions.
This finding is confirmed by examining the accumulated impact of exchange rate shocks on monetary base in levels instead of growth rates – there is no statistically significant impact on the level of base money. In contrast, structural shocks to output and prices have a statistically significant impact on base money in levels for several quarters.
The dynamics of the structural shocks do not need to seem identical to the coefficient estimates of the reduced form equations, as the structural shocks are identified by theoretical assumptions about the contemporaneous relationships between the reduced form errors. This explains why the policy reaction to the exchange rate gap is countercyclical in equation 2 but the response of base money to a structural shock in the exchange rate is largely insignificant in Figure 2.
Recent estimates support an increasing weight on the euro in the basket, but since September 2008 almost all weight appears to again go to the US dollar (see Frankel, 2009, and http://content.ksg.harvard.edu/blog/jeff_frankels_weblog/2009/03/11/the-rmb-has-now-moved-back-to-the-dollar/).
Woodford (2000) discusses problems related to excessive forward-looking reactions in monetary policy.
The People's Bank's survey on inflation expectations is highly correlated with the business survey used in our study for the 2001–2008 period, where both series are available (contemporaneous correlation coefficient of 0.83).
A possible alternative would be to use actual future outcomes for inflation and estimate a forward-looking reaction by GMM, as reported in Zhang (2009). However, our approach relies on surveys on inflation rather than a perfect foresight assumption.
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Acknowledgements
We thank Tuuli Koivu, Iikka Korhonen, participants in the 2010 American Economic Association-ASSA Annual Meetings in Atlanta, ACES session on China's exchange rate, and in the 2010 Finnish Economic Association Annual Meeting in Tampere, in particular our discussants Sushanta Mallick and Petri Mäki-Fränti, for helpful comments and suggestions. All opinions are of the authors and do not necessarily reflect those of the Bank of Finland. Any errors are our own.
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Mehrotra, A., Sánchez-Fung, J. China's Monetary Policy and the Exchange Rate. Comp Econ Stud 52, 497–514 (2010). https://doi.org/10.1057/ces.2010.16
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DOI: https://doi.org/10.1057/ces.2010.16
Keywords
- exchange rate
- hybrid McCallum–Taylor monetary policy reaction function
- SVAR
- survey-based inflation expectations
- China