Abstract
Central to this paper is the analysis of inflation dynamics in the Euro Area as well as in eleven individual Euro Area member countries between 1990 and 2012. Based on the hybrid new Keynesian Phillips curve, the analyses include survey measures from Consensus Economics to compare inflation dynamics across Euro Area member countries. Particular focus is set on the choice of suitable measures of real marginal cost. In addition to the well-known output gap, the role of finance-neutral output gaps and unemployment gaps is examined. Throughout the analyses, price setting is found to be largely backward-looking, but with a decreasing trend over time. Countries’ varying sensitivity to the different measures of real marginal cost is highlighted, which may indicate persistent heterogeneity in Euro Area inflation dynamics. With the onset of the financial crisis, finance-neutral output gaps outperform alternative measures of real marginal cost.
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Notes
EA data is calculated as the weighted average of EA11 countries based on quarterly Gross Domestic Product (GDP) weights; in the case of GDP and credit data, sums of absolute values are included.
Forecast errors are determined as mean absolute percentage errors (MAPE) and found to be smaller than 20 basis points in the majority of countries. Thus, forecasts are considered overall unbiased. The fact that forecasters themselves (among them Consensus Economics forecasters) rely on Phillips curve relationships when forming expectations on macroeconomic variables (Fendel et al. 2011) is considered a further viable justification for using Consensus Economics inflation forecasts.
An exception to the broad literature supporting survey measures of inflation expectations has been Nunes (2010) who finds the weight of rational expectations to be comparably higher and concludes that survey expectations do not correspond to ‘true’ inflation expectations.
HAC weight matrix using Bartlett (Newey-West) kernel with a lag length of four is chosen here.
Following Borio et al. (2007), the trade-weighted output gap takes into account the share of EA10 related imports relative to total imports of one country in the respective quarter. The weight is calculated based on information of the IMF Direction of Trade Database.
Correlations between the output gap and the EA-weighted output gap are >0.99 in all EA-countries. A detailed description of trade weight derivations and estimation results are available upon request.
Testing for the inflationary pressure of real effective exchange rates in a similar set-up to that of oil prices does, nonetheless, not yield significant insights into the inflation formation process. Both results are available upon request.
Testing for weak instruments indicates that the hypothesis of weak instruments can be rejected only at the >10 % confidence interval for the following countries: Austria, Finland, France, and Ireland.
Estimation results are not reported separately, but are available upon request.
Despite technical disadvantages of the HP filter compared to other filtering methods, e.g. band-pass filters, it is preferred due to the possibility of estimating it in state space form.
In line with the traditional HP filter, \(\lambda \) is set to 1600, determined by the error variances of the respective state and observation equation. In order to ensure that implicit business cycle frequencies correspond to those of the standard HP filter in the baseline specification, \(\lambda \) is set in line with Borio et al. (2014). Particular attention is paid to \(\beta \), as values close to one would estimate unit root output gaps, but, with the exception of the EA aggregate, values never approach the upper limit of 0.95.
Various additional variables may be included to represent the financial cycle, among them measures of credit quality and spreads, financial firm indicators as well as leverage and liquidity. With respect to limited availability of data for EA11 countries, preference is given to the estimation of finance-neutral output gaps for all EA11 countries, accepting a smaller set of financial cycle variables.
Due to partially short time series for residential property prices, this time series has been excluded from the observation equation when the number of observations was reduced extensively. Table 3 indicates where this is the case.
As the post-2007 data sample is still rather small, analyses are expected to be more informative as longer time series become available.
Testing for a break in 1999 (2001 in the case of Greece) in response to the changeover to the Euro indicates a decrease in \(\gamma _b\) in the majority of countries. No systematic differences are, nonetheless, observed for the role of the output gap.
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Appendices
Appendix 1: Variables and data sources
Variable | Source | Comment |
---|---|---|
Time span | ||
HICP: Inflation Year-over-year (yoy) change harmonized index of consumer prices (HICP) in % | Eurostat OECD | HICP inflation (Eurostat), beginning of 1990s complemented with CPI inflation (OECD) |
Q1 1990-Q4 2012 | ||
CHICP: Core inflation yoy change CHICP in % | Eurostat OECD | CHICP inflation (Eurostat), before 1997 complemented with core CPI inflation (OECD) |
Q1 1990-Q4 2012 | ||
IFC: Inflation expectations Survey measure of expected inflation for the current and coming year | Consensus Economics | Quarterly data based on monthly forecasts for current and coming year |
Q1 1990-Q4 2012 | ||
GAP: Output gap Deviation of GDP from HP filtered GDP in % of HP filtered GDP | Eurostat AMECO | Real GDP in mEUR seasonally adjusted and adj. by working days |
Q1 1979-Q4 2012 | ||
FNGAP: Finance-neutral output gap (1) log real credit to the private non-financial sector in bnEUR (2) log real residential property price index | OECD | Both time series are demeaned using Cesàro means |
Q1 1990-Q4 2012 | ||
UGAP: Unemployment gap Deviation of the harmonized unemployment rate from its structural level | OECD | Annual NAIRU estimates (OECD) for four quarters of the respective year |
Q1 1990-Q4 2012 | ||
OIL: Oil price Crude oil, Brent in EUR yoy growth in % | Thomson Reuters Ecowin | Quarterly oil price corresponds to three-month averages |
Q1 1990-Q4 2012 | ||
NULC: Nominal unit labour cost yoy change in NULC in % | Eurostat AMECO | Seasonally adjusted and adj. by working days (Eurostat), complemented with AMECO data |
Q1 1990-Q4 2012 | ||
RULC: Real unit labor cost yoy change in RULC in % | Eurostat AMECO | Seasonally adjusted and adj. by working days (Eurostat), complemented with AMECO data |
Q1 1990-Q4 2012 | ||
I3M: Short-term interest rate 3-month Euribor/3-month money market rates in % | Eurostat | 3-month money market rates before 1999 |
Q1 1990-Q4 2012 | ||
I10Y: Long-term interest rate 10-year government bond interest rates | Eurostat | EMU convergence criterion bond yields |
Q1 1990-Q4 2012 | ||
SPREAD: Interest rate spread Difference between long- and short-term interest rates | own calculations | – |
Q1 1990- Q4 2012 | ||
REERL/REERC: Real effective exchange rate Index (level values) or yoy growth in % | BIS | Index values or yoy growth included depending on correlation statistics |
Q1 1990-Q4 2012 | ||
CAPAL/CAPAC: Capacity utilization Share of total in % or yoy growth in % | European Commission | Business and Consumer Survey, question #13; index values or yoy growth included depending on correlation statistics |
Q1 1990-Q4 2012 |
Appendix 2: Baseline specification rolling regression estimation results
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Amberger, J., Fendel, R. Understanding inflation dynamics in the Euro Area: deviants and commonalities across member countries. Empirica 44, 261–293 (2017). https://doi.org/10.1007/s10663-016-9322-x
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DOI: https://doi.org/10.1007/s10663-016-9322-x