Abstract—
The article compares the effectiveness of various monetary policy regimes in terms of controlling inflation. It is shown that the hybrid inflation targeting regime, which combines the management of inflation as the main goal and the exchange rate as an additional one, makes it possible to simultaneously reduce the volatility of both inflation and the exchange rate. Thus, it is preferable to the pure inflation targeting regime in order to ensure the stability of the financial conditions for the development of the economy. Hypothesis testing was carried out by modeling the joint dynamics of inflation, exchange rate, and oil price volatilities in the VAR model. Volatility estimates were obtained using EGARCH models on monthly data for the period 1980–2021, for oil prices, 1992–2021, for the consumer price index, and 1995–2021 for the exchange rate.
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In [14], the behavior of various volatility models was studied and showed that in terms of predictive abilities, the GARCH model is in no way inferior to the ARCH models. GARCH models are less demanding and more accurate than ARCH. When analyzing financial and macroeconomic time series, the GARCH (1.1) small-order model is usually used.
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Appendix A
Appendix A
The results of estimation of the VAR-model of the joint volatility dynamics, full specification
Index | Dependent variable | ||
---|---|---|---|
\(Vol\_in{{f}_{t}}\) | \(Vol\_e{{r}_{t}}\) | \(Vol\_oi{{l}_{t}}\) | |
\(Vol\_in{{f}_{{t - 1}}}\) | 0.93*** | ||
(0.0233) | |||
\(Vol\_e{{r}_{{t - 1}}}\) | 0.090*** | 0.901*** | |
(0.027) | (0.033) | ||
\(Vol\_oi{{l}_{{t - 1}}}\) | 0.032 | 0.075 | 0.949*** |
(0.044) | (0.069) | (0.013) | |
\(inf\_cycl{{e}_{t}}\) | 0.304 | ||
(0.689) | |||
\(\log \left( {e{{r}_{t}}} \right)\) | 0.002 | –0.007 | |
(0.004) | (0.006) | ||
\(\log \left( {oi{{l}_{t}}} \right)\) | 0.0014 | –0.003** | –0.003*** |
(0.0012) | (0.002) | (0.0008) | |
\(d\_09\_13\) | –0.273*** | 0.294** | 0.008 |
(0.091) | (0.135) | (0.039) | |
\(d\_14\_16\) | –0.309** | 0.444* | –0.022 |
(0.171) | (0.234) | (0.044) | |
\(d\_17\_21\) | –0.326** | 0.360* | –0.034 |
(0.182) | (0.278) | (0.034) | |
R2 | 0.90 | 0.88 | 0.89 |
Residual sum of squares | 12.9 | 40.3 | 7.4 |
Mean value of dependent variable | –10.9 | –6.6 | –4.3 |
Standard deviation of dependent variable | 0.79 | 1.28 | 0.55 |
Covariance determinant of random error matrices | 0.000412 | ||
Logarithmic maximum likelihood function | –62.5 | ||
AIC | 0.788 | ||
SIC | 1.120 | ||
Number of coefficients | 21 | ||
Number of constraints | 6 | ||
***, **, and * are the significance levels of 1, 5, and 10%, respectively. In parentheses under the estimated coefficients are their standard errors. |
Appendix B
Analysis of the Impulse-Responses Functions
The analysis of the impulse-responses functions was carried out according to the most complete specification of the model in order to avoid the exclusion of important relationships during their construction. Function graphs are shown in Fig. 2. A significant response of inflation volatility to a shock (single innovation) of exchange rate volatility is delayed, begins to operate from the second month and continues for 20 months. A similar response of inflation volatility is also observed to the shock of oil price volatility, however, it is somewhat lower in level. The response of exchange rate volatility to an oil price volatility shock is immediate and remains significant for 8 months. A significant inertial response of inflation volatility to its own shock persists for 14 months, for the exchange rate for 12, and for oil prices for 20 months.
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Medvedev, I.D. Comparison of the Efficiency of Pure and of Hybrid Inflation Targeting from the Point of View of Inflation Control. Stud. Russ. Econ. Dev. 34, 274–283 (2023). https://doi.org/10.1134/S1075700723020089
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DOI: https://doi.org/10.1134/S1075700723020089