Expanding the Labor Market Lens: Two New Eurozone Labor Indicators

Board of Governors of the Federal Reserve System International Finance Discussion Papers ISSN 1073-2500 (Print) ISSN 2767-4509 (Online) Number 1415 August 2025 Expanding the Labor Market Lens: Two New Eurozone Labor Indicators Ece Fisgin, Joaquin Garcia-Cabo, Alex Haag, and Mitch Lott Please cite this paper as: Fisgin, Ece, Joaquin Garcia-Cabo, Alex Haag, and Mitch Lott (2025). “Expanding the Labor Market Lens: Two New Eurozone Labor Indicators,” International Finance Discussion Papers 1415. Washington: Board of Governors of the Federal Reserve System, https://doi.org/10.17016/IFDP.2025.1415. NOTE: International Finance Discussion Papers (IFDPs) are preliminary materials circulated to stimulate discussion and critical comment. The analysis and conclusions set forth are those of the authors and do not indicate concurrence by other members of the research staff or the Board of Governors. References in publications to the International Finance Discussion Papers Series (other than acknowledgement) should be cleared with the author(s) to protect the tentative character of these papers. Recent IFDPs are available on the Web at www.federalreserve.gov/pubs/ifdp/. This paper can be downloaded without charge from the Social Science Research Network electronic library at www.ssrn.com.

Expanding the Labor Market Lens: Two New Eurozone Labor ∗ Indicators Ece Fisgin † Joaquin Garcia-Cabo ‡ Alex Haag§ Mitch Lott¶ July 31, 2025 Abstract Wepresentaprincipalcomponentanalysisofeuroarealabormarketconditionsbycombining informationfrom 22 labor market indicators intotwo comprehensive series. Thesetwonovel indicators provide a systematic view of the current state and forward-looking direction of the euro-area labor market, respectively, and demonstrate superior forecasting performance compared to existing indicators. Crucially, we find significant implications for monetary policy design: a local projection analysis reveals that ECB monetary policy shocks have attenuated effects on both inflation and unemployment when the labor market forwardlookingindicatorishigh. Thedampenedinflationresponsecallsfortighterpolicyratepaths than a standard Taylor rule would prescribe. Finally, we show that focusing solely on the official unemployment rate may understate the actual labor market slack, and consequently, the trade-off between labor market health and inflationary dynamics. JEL Classification: E24, E27, J63 Keywords: employment, unemployment,labormarketforecasting,europeanlabormarkets ∗The views expressed in this paper are solely our responsibility and should not be interpreted as reflecting the views of the Board of Governors of the Federal Reserve System or of any other person associated with the FederalReserveSystem. WeareextremelygratefultoArpitaChaterjee,E´tienneGagnon,NilsGoernemann,and participants at the AFE/EME Brownbag at the International Finance Division in the Federal Reserve Board for their comments and suggestions. †Division of International Finance, Federal Reserve Board. Email: ece.fisgin@frb.gov. ‡Corresponding author. Division of International Finance, Federal Reserve Board. Email: joaquin.garciacaboherrero@frb.gov. §Division of International Finance, Federal Reserve Board. Email: alex.j.haag@frb.gov. ¶University of Southern California. Email: mitchlott2017@gmail.com.

1 Introduction Labormarketconditionsplayacrucialroleinshapingeconomicgrowthandinformingmonetary policy decisions. Many central banks, including the Federal Reserve and the European Central Bank (ECB), rely on labor market indicators to identify underlying inflationary pressures and gauge overall economic health in guiding their policy choices. Such indicators by themselves, however, may create a puzzling picture of the job market. As a result, policymakers may need to look at a broad set of indicators to extract the correct signal about the health of the market.1 Moreover, traditional measures such as employment and unemployment rates are inherently backward-looking and come with a lag. This limitation is especially acute for euro area countries, where labor force surveys are usually released on a quarterly basis, potentially leading to delayed policy analysis. While some forward-looking measures exist, they often fail to directly address the specific labor market conditions most relevant to policymakers. In this paper, we present a systematic approach for analyzing euro area labor market conditions by combining information from 22 labor market indicators into two comprehensive indicators via principal component analysis: level and momentum.2 The first indicator, which we define as level, effectively captures historical trends, including the impacts of the Eurozone Sovereign Debt Crisis and the COVID-19 pandemic. The second indicator, which we call momentum, is forward-looking and adept at detecting changes in labor market dynamics. These two labor market indicators offer policymakers a more comprehensive and real-time view of labor market dynamics compared to traditional single-variable measures to better inform policy choices. Our findings reveal that the momentum indicator outperforms existing forward-looking measures in predicting changes in unemployment rates. Furthermore, we demonstrate that labor market momentum significantly influences the transmission of monetary policy shocks to inflation and unemployment. Specifically, higher labor market momentum dampens the impactofmonetarytighteningonunemploymentandinflation,potentiallyaffectingtheexpected outcomes of policy interventions. The methodology employed in this study combines a wide range of labor market indicators from various statistical offices including Eurostat, the ECB, and the European Commission. We use principal component analysis (PCA) to distill information from these 22 variables into two main components at the quarterly frequency from 2010:Q2 onwards: level and momentum. While the indicators provide quarterly values, they are updated in real-time as monthly information refines the model estimates. We assess the robustness of our model through alternative specifications, includingalongertimeserieswithfewerincorporatedvariables. Allspecifications effectivelycapturetheturnsoftheeuro-arealabormarketduringimportantrecentepisodessuch as the Eurozone Debt Crisis and the COVID-19 pandemic. We conduct several forms of analysis to demonstrate the practical applications of our indicators. We start by comparing the forecasting accuracy of our momentum indicator against existing forward-looking measures of labor market health, such as the European Commission’s Employment Expectations Indicator (EEI) and the European Labor Market Barometer (LMB). TheresultsindicatethatourmomentumindicatoroutperformsbothEEIandLMBinpredicting future changes in the unemployment rate across several specifications and sampling periods. Wethenexploretheinfluenceofmomentumontheresponsesofinflationandunemployment 1Forinstance,formerFedChairJanetYellenpopularized“JanetYellen’sdashboard,”asetof12labormarket and wage indicators: https://www.brookings.edu/articles/introducing-janet-yellens-dashboard. 2Our model is a euro-area application of the Kansas City Fed Labor Market Index: https://www .kansascityfed.org/data-and-trends/labor-market-conditions-indicators. 2

toECBmonetarypolicyshocksfromJarocin´skiandKaradi(2020)usinglocalprojections(Jord`a, 2005). Thisanalysisrevealsthathighlabormarketmomentumsignificantlydampenstheimpact of monetary tightening on both inflation and unemployment. We then test the implications for monetary policy design using a calibrated Taylor rule. We demonstrate that periods of strong labor market momentum result in higher policy rates compared to the path that would emerge from a standard Taylor rule when the responses of inflation and unemployment abstract from labor market momentum. These findings underscore the importance of considering the strength and direction of the labor market when designing optimal monetary policy responses. Lastly,andgiventheimportantrelationshipbetweenunemploymentandinflation,weinvestigate how our model-based measures of labor market slack compare to traditional measures in the context of Phillips Curve estimations. Our results indicate that the model-based unemployment rate exhibits a stronger negative relationship with inflation than official unemploymentbased measures of slack, suggesting that focusing solely on the official unemployment rate may understate the actual trade-off between labor market health and inflationary dynamics. Our study, incorporating a wide range of variables and leveraging advanced statistical techniques, offers economists and policymakers a flexible and robust tool for real-time analysis. The applications demonstrated in this research highlight the potential use cases for these indicators to enhance monetary policy decision-making and deepen our understanding of labor market dynamics in the euro area. As central banks continue to navigate complex economic landscapes, there is outstanding value in developing tools that offer novel insights into labor market conditions when crafting effective monetary policy responses. 2 Related literature This paper contributes to two main strands of literature. First, we contribute to the existing literature that aims at combining labor market data efficiently using econometric methods for policy analysis. For instance, and most related to our approach, Hakkio and Willis (2013) use a principal component analysis (PCA) approach to develop the monthly Kansas City Fed Labor Market conditions indicator, currently consisting of 24 U.S. labor market variables. This model has provided timely analysis since its inception (Glover et al., 2021). Additionally, Barnes et al. (2007) construct a statistical summary of U.S. labor market variables by applying PCA and demonstrate that wage pressures in recent years correlate better with their measure than with the standard unemployment rate gap, though their measure does not necessarily perform better when focusing on the historical behavior of prices. Chung et al. (2015), using a dynamic factor model, and more recently Gilchrist and Hobijn (2021) via PCA, are other examples using a myriad of labor market variables to summarize economic trends. Our paper complements this literature by analyzing the euro area labor market by implementing a PCA approach. The euro area is composed of 20 European countries sharing a common monetary policy but different fiscal authorities. To our knowledge, we are the first paper to use this procedure for an economy withalaborforceofabout200millionworkersandfacingdifferentlabormarketinstitutionsand policiesthantheUnitedStates(Garc´ıa-Caboetal.,2023). Fortheeuroarea,theclosestavailable indicators are the European Labor Market Barometer, a survey based measure of 17 European countries on unemployment and employment perspectives and the Employment Expectations Indicator (EEI) from the European Commission. Our approach offers a complementary view by incorporating hard data releases for the aggregate euro area economy as well as individual countries in a timely fashion, allowing for real-time analysis and forecasting of labor market conditions. Second,tostudytheeffectsofsuchshocksonlabormarketvariables,wefollowtheliterature 3

measuring the effect of monetary policy shocks, specifically for the euro area. We focus on surprises in European Central Bank’s (ECB) monetary policy, the common euro area monetary policy authority, as identified in Jarocin´ski and Karadi (2020), from whom we obtain a series of monetary policy surprises in response to 280 ECB policy announcements during the period January 1999 through December 2024. There is ample evidence of the transmission of monetary policyshockstohouseholds(seeforinstanceCloyneetal.(2019)andHardingandKlein(2022)), as well as the interaction of the transmission with different household variables such as savings (Ferreira et al., 2025). Our work expands on this literature by studying how macroeconomic variables interact with the state of the labor market and how monetary policy transmission is dampened when labor markets are tight. 3 A Principal-Component Analysis: Two indicators This section describes variable selection for our analysis, including sources, time frame covered, and variable normalization. We then turn to describe how we create our baseline indicators using Principal Component Analysis and provide some robustness analysis. 3.1 Data sources Our dataset leverages a wide range of labor market indicators from different statistical offices, includingtheStatisticalOfficeoftheEuropeanUnion(Eurostat)andtheECBandtheEuropean Commission,whichwemostlyobtainviaHaverAnalytics. Wepresentthefullrangeofindicators and sources in Table A.1. We first include a set of traditional quarterly indicators like the unemployment plus underemployment rate, underemployed due to involuntary part-time work, long-term unemployment, total hours and hours worked per person, job vacancy rate, employment rate, employmentto-population ratio, labor force participation rate, labor market transition flows, ECB Survey of Professional Forecasters (SPF) euro area unemployment rate forecast (at 8 months ahead), long-term unemployment, and temporary contracts. We supplement this with monthly indicators aggregated to quarterly averages. Among these monthly releases, we consider several forward-looking measures such as the labor hoarding indicator3, and the HCOB Eurozone Manufacturing and Services Employment PMI. We also include several country-specific indicators for the largest euro-area economies, including individuals actively seeking work from the French Ministry of Labor (Ministre du Travail, de l’Emploi et de l’Insertion), Kurzarbeit Notices (Short-Time Work Allowance) from the German Federal Employment Agency (Bundesagentur fu¨r Arbeit), and Cassa Integrazione Guadagni (Wage GuaranteeFund)fromtheItalianNationalInstituteforSocialSecurity(IstitutoNazionalePrevidenza Sociale) which support firms to maintain employment levels during economic downturns. Finally, we also incorporate the forward-looking Employment Expectations Indicator (EEI) from the European Commission, a composite measure of managers’ hiring intentions across key sectors, standardized to reflect deviations from historical employment expectations. 3The European Commission’s Labor Hoarding Indicator (LHI) combines responses to two pre-existing questions on expectations with respect to employment and output in the coming 3 months from various surveys associated with its Joint Harmonized EU Programme of Business and Consumer Surveys. The Commission defines labor hoarding as when “firms expect their output to decrease, but their employment to remain stable or even increase.” 4

3.2 Series normalization and time frame Our baseline analysis defines a unit of observation at the quarterly frequency. For indicators available at the monthly level, we construct the quarterly counterpart by averaging monthly indicators into quarters. All variables are seasonally adjusted. We perform additional checks to ensure homogeneity and consistency of our series. First, when a quarter’s final monthly observation is missing, we carry forward the most recent value to complete the quarter. Second, all variables are standardized to have zero mean and unit standard deviation, allowing comparability across indicators. For easier interpretation, countercyclical variables are inverted so that higher values consistently reflect labor market improvement, such as unemployment or labor hoarding. Third, a limited set of variables with short time histories are backcasted to extend coverage using linear regressions on related indicators with longer histories.4 With the resulting data, we construct two baseline models: one that begins in 2010:Q2 and extends to 2025:Q2 that employs all variables discussed, and a longer model that extends from 2004:Q2 to 2025:Q2 and considers a subset of data available for all years in the range. 3.3 Principal component estimation We next combine the information from the 22 variables using a Principal-Component analysis for our baseline model. The time series is thus limited by the latest starting point of the series, and as such the baseline model comprises data from 2010:Q2 until 2025:Q2. We subsequently assess the robustness of the model by extending the period analyzed, albeit in a smaller model. A first inspection of the estimated components conveys that the first two components account for about 80 percent of the total variance of the data.5 This result is in line with Hakkio and Willis (2013) for the United States. As such, we keep these first two components, which we then rotate using the varimax method and we predict the scores to obtain two indicator series, the main result of this section. The variables with the largest contributions to the first component are correlated with the levelorcurrenthealthoftheeuroarealabormarket,whilethosewiththelargestloadingsforthe second component have a more forward-looking flavor, as presented in Table 1.6 In particular, thefirstcomponentobtainsthelargestcontributionsfromvariablesregardingthecurrentstateof the labor market, namely the unemployment and employment rate, the employment-population ratio, current measures of underemployment and long-term unemployment, as well as the unemployment rate forecast from the Survey of Professional Forecasters. The second component loads largely from forward-looking employment surveys, measures of short-time work and labor under-utilization, as well as hours worked which are a flexible way of adjusting labor utilization in the intensive margin. As a result of these differences in loadings, with the first component capturing the overall level or current health of the euro area labor market, and the second one the more-forward looking direction, we follow Hakkio and Willis (2014) and refer to these rotated components as the “level” and “momentum” indicators, respectively. We next highlight some similarities and differences between the United States and the euro area resulting indicators. In the case of the UnitedStates,HakkioandWillis(2014)showthatthelevelcomponentexhibitslargecorrelations 4Webackcastfor2004:Q2-2007:Q4theunemployment+underemploymentrateU6betweenusingtheunemploymentrate,andKurzarbeitNoticesusingthelaborhoardingindicatorforGermany;andthejobvacancyrate for 2004:Q2-2005:Q4 using the non-agricultural vacancy rate. These sources are presented on Table A.2. 5Wepresenttheeigenvaluesandpercentageofvarianceexplainedforthefirst10componentsinTableA.3in the Appendix. 6We present the loadings for the full set of variables on Table A.4 in the Appendix. 5

Component 1 Component 2 Unemployment Rate EA Labor Hoarding Employment-Population Ratio Kurzarbeit in Germany Employment Rate Services Employment PMI Unemployment + Underemployment Rate Cassa Integrazione in Italy Long-term unemployment rate Hours Worked per Employed Person SPF Unemployment Rate Forecast Employment Confidence Survey Table 1: Variables with largest loadings for each component withmeasuresofunemploymentandjobseparations, aswellaslong-termunemployment, inline with our findings for the euro-area labor market. For the United States, the largest contributor tothemomentumindicatoristheISMmanufacturingemploymentindex. InourestimatedPCA for the euro area, both services and manufacturing PMI employment indexes are also largely correlated with the momentum indicator. Notwithstanding, the large loadings from measures of short-time work and labor hoarding for the euro area highlight an important difference across U.S. and euro-area labor market institutions. Given the stringent labor market legislation in many euro-area countries, policy-makers have relied in short-time work programs to protect employment in recent downturns. Since hiring and firing costs are significant, the job-finding rate is lower than in the United States, making increases in unemployment very persistent, and as such, these policies protect jobs (Garc´ıa-Cabo et al., 2023). In the United States, where labor market flexibility tends to be higher, firms lay off workers and recall them with little cost, reducing the popularity and usage of short-time work policies. Our PCA analysis validates the incorporation of variables that capture labor market institutions differences to fit the data when applying these methods in a cross-country setting. Having described some of the most salient differences across labor markets, we next turn to describe the historical evolution of the estimated indicators for the euro area. 3.4 A historical overview of level and a momentum indicators Figure1depictsthequarterlyevolutionofthelevelandmomentumindicatorsbetween2010and 2025. Our baseline indicators start during the brief expansion in 2010 that followed the 2008 financial crisis, right before the euro area Sovereign Debt Crisis in 2011.7 The level indicator (solid blue line), while recovering during 2010 and early 2011, was still below its long runaverage, and it dipped to its historical trough during the first half of 2013, coinciding with an unemployment rate peak of 12.2 percent and the employment rate at a multi-decade low of 55.7 percent. From this trough, the level indicator started a prolonged recovery, turning positive at theendof2017,thatlasteduntilthefirstquarterof2020,whentheCOVID-19shockhit. During theCOVID-19pandemic,theindicatorquicklyturnednegative,butthiscollapsewasshort-lived, as governments put in place extensive fiscal policies, including labor market subsidies to keep workersattachedtofirms, thatallowedthemarkettoabsorbthelabormarketshockbetterthan in 2011-2012. The latest data suggest that the activity indicator was at the beginning of 2025 at its historical peak, coinciding with the lowest historical record of unemployment in the euro area and high levels of employment and labor force participation. We next turn to describe the momentum indicator (dashed orange line). As a result of the increased optimism about the economy rebounding from the 2008 recession, at the beginning of thesampleitsignaledapositiveforward-lookingsentiment,aboveitslong-runaverage. However, it quickly turned negative, and only returned to above long-run average levels in 2015. The 7Weassesstherobustnessoftheseindicatorsandalleviatethedatahorizonlimitationsbyestimatingasmaller model with longer time series later. 6

momentum indicator progressively improved until the end of 2017, when it started a downward trend, although still in positive territory, amid a slow down in growth and a deterioration in some regional labor markets, such as Germany. Interestingly, in turned negative in 2020:Q1, before the level activity reflected the COVID-19 effects on the labor market, and it collapsed in 2020:Q2 to then briefly rebound in 2021. Since 2023, it has been below trend, but fairly stable as consumer sentiment weighed on growth amid high inflation, and moderating employment growth continue weighing on labor demand. All in all, by combining information from multiple euro-area labor market variables into level and momentum indicators, we provide a more comprehensive and forward-looking view of labor market conditions than any single indicator could offer. We next assess the robustness of these estimators through alternative model specifications. Figure 1: Euro-area Labor Market Indicators 3.5 Robustness of the estimators: alternative specifications Wenowconsideranalternativespecificationinvolvingalongertimeframebutasmallernumber of variables to assess the robustness of the baseline estimator. In particular, we now restrict the model to a subset of 13 variables starting in 2004:Q2: manufacturing and services employment PMIs, hours worked per person employed, total hours worked in the industry sector excluding construction, the job vacancy rate, the unemployment + underemployment rate, the unemployment rate, the SPF unemployment rate forecast, the French job seekers, the registered unemployed in Spain, the number of workers under kurzarbeit program in Germany, and the European Commission’s labor hoarding and employment confidence surveys. The alternative indicators, presented in Figure 2, track the behavior of the baseline model very closely, alleviating concerns on the long-run behavior of both indicators due to the orthog- 7

onalization assumptions on shorter time series. We highlight some slight differences next. First, the alternative model’s first two components explain just about 70 percent of the variance, compared to 82 percent on the baseline given the inclusion of a larger set of variables. Second, the level indicator in the smaller alternative model exhibits slightly less variance, with its trough during the sovereign debt crisis and its current peak lower than what the baseline indicator suggests. This is because the baseline model incorporates variables with large loadings that reflect labor market health, such as the employment rate or the employment-to-population ratio. Abstracting from these variables results in a understatement of the state of the labor market. Third, the alternative momentum indicator was virtually identical to the baseline between 2010 and 2015, but it somehow was a bit less optimistic than the baseline in the recovery post-2015. Note how the main loadings into the baseline are almost the same as under the alternative, with theexceptionofCassaIntegrazione, onlyavailablestarting2009. Thecollapseofthemomentum indicator under both models was similar during COVID-19, and more recently, the alternative model has consistently been below its long-run average compared to the baseline. This reflects larger loadings from hours worked per person relative to the baseline, which have failed to recoversincetheCOVID-19pandemicasmeasuresofhoardinghaveremainedsignificant. Overall, due to its explanatory power and qualitative behavior, which incorporates information from key labor market variables, this analysis demonstrates a clear preference for the baseline model. Figure 2: Euro-area Labor Market Indicators: Baseline and alternative specification Note. Baselinemodelreferstothe22variablemodelspanning2010:Q2-2025:Q2. Alternativemodelrefers to the 13 variable model described in Section 3.5, spanning 2004:Q2-2025:Q2. Ofnote,themodel’sflexibilityandrobustnessproveparticularlyvaluableifaresearcherwas interested in assessing how individual variables are affecting indicator dynamics. In particular, onecouldestimatealternativemodelsbyexcludingcertainvariables. Whilethisapproachwould notprovideanexactanalysisofvariablecontributions,itcanofferimportantinsightsintotherecentbehaviorofbothlevelandmomentumindicatorsvis-`a-visvariablesofinterest. Thismethod 8

provides anuancedunderstanding oflabor market dynamics, identifying andinterpreting trends more effectively. Ultimately, the baseline model’s comprehensive nature and adaptability make it a powerful tool for real-time labor market analysis and informed decision-making. 4 Applications The following section showcases key applications of our developed indicators. First, we demonstrate the superior forecasting capabilities of the momentum indicator compared to existing forward-looking measures of labor market health. This comparison underscores the indicator’s value in providing timely and accurate assessments of current labor market conditions. Subsequently, we explore the significant influence of momentum on the responses of inflation and unemployment to monetary policy shocks. Our analysis reveals that the momentum indicator plays a crucial role in shaping these macroeconomic responses, highlighting its importance for optimal monetary policy design. 4.1 Level and momentum and the business cycle We first assess the effectiveness of indicators as predictors of changes in unemployment and how they compare against existing composite measures of labor market health. Our analysis primarily focuses on the European Commission’s Employment Expectations Indicator (EEI), chosen for its extensive time series and timely updates. We also consider the European Labor Market Barometer (LMB), as well as its subcomponent focused on unemployment, though these results are relegated to the appendix. For context, the EEI is a weighted average of managers’ employment plans across retail trade, construction, industry, and services sectors, designed to forecast general employment trends. This approach aligns closely with our momentum indicator’s aim of capturing early labor market signals. By comparing our indicator’s performance against the EEI, we can not only validate our methodology but also highlight the potential advantages of our more comprehensive, data-driven approach over traditional survey-based measures. We start with a simple regression framework: J (cid:88) ∆Urate = α+ β ∆Momentum +Z +e (1) t j t−j t t j=1 where the dependent variable ∆Urate is the contemporaneous change in the euro area t unemployment rate from the previous quarter. We include as regressors the lagged change in momentum (with j indicating the first or second lag, depending on the specification) captured by∆Momentum , andaseriesofCOVIDdummyvariablesZ . Werunthesamespecification t−j t for the European Commission’s EEI for comparison. We use the fitted estimated regressions to predict the change in the euro area unemployment rate for both series and assess each series’ forecasting ability using the root mean squared error (RMSE) of each series’ forecasts. Our baseline exercise compares momentum and EEI for the period 2005:Q1–2019:Q4, using one lag for momentum, our preferred specification as a shorter lag is more likely to represent signal on near-term future labor market dynamics, with additional lags tested for robustness in the appendix. 8 8Forthisexercise,weusetheestimatedmomentumcomponentfromthebaselineprincipal-componentanalysis butwespliceitbackto2004usingthesmallermodeltoincreasethenumberofobservations. Weincludeadditional comparisons for a 2010:Q2–2019:Q4 sample and the 2010:Q2–2025:Q1 sample including the COVID-19 crisis in 9

Wepresent the resultsof thisanalysis inFigure 3, panel(a). Our in-samplebaseline prediction exercise shows that the momentum indicator performs slightly better than the employment expectations index (RMSEs of 0.178 versus 0.19). These results are robust to the second lag of our indicator, shown in the appendix, with RMSEs of 0.195 for momentum and 0.197 for EEI, respectively, although both indicators underperform relative to the first lag specification. In the appendix, we show similar results for alternative specifications using the European Labor Market Barometer (LMB) and its unemployment subcomponent (CompA), with our LMI indicator outperforming both for in-sample prediction. 9 We also demonstrate LMI’s superior out-of-sample forecasting ability using an expanding window 1-step ahead forecast. We use an initial window of 40 quarterly observations (roughly 2/3rdsofavailabledata). OurresultsinFigure3, panel(b)showthatourLMIindicator(RMSE = 0.195) continues to outperform EEI (RMSE = 0.210). Our results are robust to additional window specifications ranging from 30-55 observations, as well as an alternative rolling window specification. While the Momentum LMI indicator RMSE is roughly an 8 percent improvement, on average, over the EEI indicator RMSE, we note that we do not find a statistically significant resultwhentestingthedifference intheforecasterrorsusingthemodifiedDiebold-Marianotest. This may, at least in part, be due to the relatively low sample size for each of our forecast errors due to data constraints. As a result, we are confident that the momentum indicator can be used as a predictor for business cycles, as it performs at least as good or better than other existing indicators by incorporatingadditionallabormarketinformation. Moreover,duetothefactthatitincorporates forward-looking information as it is released, it is very timely, adjusting faster than waiting for a specific indicator releases, which usually come with a lag. Figure 3: Predicted changes in unemployment (a) In-Sample (b) Out-of-Sample Notes. Chart shows the extended sample results, which extends from 2005Q1 through 2019Q4. Out-ofsample is based on an expanding window 1-step ahead forecast with an initial window of 40 observations. LMI stands for the euro-area Momentum Labor Market Indicator developed in this paper, EEI for the European Commission’s Employment Expectations Indicator. the Appendix. 9In the Appendix we show that LMI also outperforms the EEI for 2010:Q2-2019:Q4 and that during the COVID-19periodbothindicatorshaveavirtuallyidenticalperformance,butthefitisnotgreatoutside2020–2022, sincethesimplelinearregressiondoesnotdoagoodjobinfittingthelargeswingsobservedduringthisperiod. We alsoshowthatLMIoutperformsotherindicators,suchastheaggregateoftheEuropeanLaborMarketBarometer and its unemployment component, over the varying time horizons discussed. 10

4.2 Momentum and monetary policy transmission The evolution of broad labor market conditions aside from the unemployment rate has been shown to be important drivers of monetary policy design (Campolmi and Gnocchi, 2016). The European Central Bank (ECB), while not having a explicit mandate on employment unlike the Federal Reserve, often cites labor market conditions as a motivating factor in determining monetary policy via the economic outlook.10 We now turn to empirically document that the level of labor market momentum can lead to different monetary policy implementations. To address this question, we estimate local projections using high-frequency monetary policy shocks from the ECB on macroeconomic aggregates, with a focus on headline inflation and the unemployment rate. Our approach includes a novel interaction of the monetary policy shock on the level of the momentum indicator. We next show how incorporating this interaction results in significantly different responses of inflation and unemployment, which will affect the appropriate monetary policy rule. In particular, we estimate a standard local projection equation, as pioneered in (Jord`a, 2005): ∆y = αh+βhεm+βh(Momentum Indicator )×εm+γhZ +e (2) t+h|t−1 1 t 2 t t t−1 t+h where εm are the daily monetary policy shocks measured in Jarocin´ski and Karadi (2020), t between January 2004 and December 2024, and aggregated at the quarterly level and standardized.11 Z is a set of controls that includes three lags of quarterly year-over-year headline t−1 HICP inflation for the euro area, quarterly official euro area unemployment rate, the end-ofquarter ECB deposit rate, and the log difference of quarter-over-quarter GDP. We additionally include a time trend control and dummy fixed effects for the COVID-19 pandemic. We interpret our coefficients of interest, βh and βh next. First, βh captures the standard response of the 1 2 1 dependent variable at horizon h after the monetary policy shock. Second, and one of the contributions in this paper, βh captures the dynamic effect associated with the interaction of the 2 period’s forward-looking momentum indicator with the monetary policy shocks at each horizon h.12 We will refer this effect as the dampening effect, referring to the marginal dampening effect that high momentum has on monetary policy shocks We focus on the effect of monetary policy shocks on the unemployment rate, inflation, and the employment rate in the euro area due to theirimportanceformonetarypolicydesign,andwerelegatetheimpactonothermacroeconomic variables, namely labor force, nominal compensation, and hours worked, to the Appendix. 10See for instance, www.ecb.europa.eu/press/press conference/monetary-policy-statement/2025/html/ ecb.is250417~091c625eb6.en.html 11WeaggregatethedailysurprisesatthequarterlylevelwithamovingaveragestructurefollowingGertlerand Karadi (2015). We then normalize the shock so it has a standard deviation of one, resulting in a mean value of the shock of about 28 basis points. 12Forthisexercise,weusetheestimatedmomentumcomponentfromthebaselineprincipal-componentanalysis but we splice it back to 2004 using the smaller model to increase the number of observations. 11

Figure 4: Local projection analysis: Unemployment Rate (a) Average Effect (b) Dampening Effect Note. Lightshadedareasrepresent90percentconfidenceintervals,darkshadedareasrepresent68percent confidence intervals, and the solid line represents the mean value. Figure 4 depicts the unemployment rate response to a monetary policy shock. Panel 4a shows that, unconditionally and standard in the literature, a tightening monetary policy shock increasestheunemploymentratebyuptoaround0.25percentagepointswiththeeffectspeaking four quarters after the shock, and exhibiting persistence beyond a year. The estimated dampening effect of momentum, as shown in Panel 4b, is negative and significant the quarter after the shock, exhibiting some persistence albeit at small significance levels. This result implies that when momentum is high, the impact on the unemployment rate might be smaller than one could have anticipated if only looking at the average effect following the shock. Examining the employment rate–the flip side of the labor market–we observe that a monetary tightening shock negatively impacts euro-area employment (Figure 5). Notably, panel 5b shows that a higher momentum significantly dampens the initial decline in employment following the shock. Specifically, a one-point increase in the momentum indicator nearly offsets the initial impact of the monetary policy shock on employment. These findings underscore the critical role of labor market momentum in determining the responses of both unemployment and employment to monetary policy shocks. High labor market momentum appears to act as a buffer, attenuating the immediate effects of tightening measures. This interaction between monetary policy and labor market dynamics has potential implications for inflation trajectories, a relationship we will explore next. 12

Figure 5: Local projection analysis: Employment Rate (a) Average Effect (b) Dampening Effect Note. Lightshadedareasrepresent90percentconfidenceintervals,darkshadedareasrepresent68percent confidence intervals, and the solid line represents the mean value. Of particular interest is the impact of monetary policy shocks on inflation, especially considering how these effects may be affected by labor market momentum. Figure 6 illustrates our findings on this crucial relationship. Panel 6a shows that a monetary policy shock reduces inflation contemporaneously by approximately 0.2 percent, with the effect persisting for four quarters and reaching a peak of about 0.35 percent. This aligns with previous research and the intended outcomes of monetary tightening. Notably, panel 6b reveals a surprising result: high labor market momentum is positively correlated with a dampening effect on inflation. Take for instance the change of the momentum indicator by one positive unit. This implies a reduction in inflation during the first year after the shock that is 10 percent lower than the average effect, with this effect persisting for nearly two years. Our findings suggest that commonly used indicators, such as employment and unemployment rates, may not be sufficient to capture labor market health for central bankers’ purposes. This points to the likely existence of labor market state-dependence in macroeconomic dynamics, including inflation. A better understanding of the macro responses depending on the state of the economy, as captured by our momentum indicator, can significantly influence the design and transmission of monetary policy. We next explore this channel by demonstrating how accounting for the dampening effect of our labor market momentum indicator can lead to different monetary policy responses using standard Taylor Rule principles. 13

Figure 6: Local projection analysis: Inflation (a) Average Effect (b) Dampening Effect Note. Lightshadedareasrepresent90percentconfidenceintervals,darkshadedareasrepresent68percent confidence intervals, and the solid line represents the mean value. 4.2.1 Taylor Rule Implications Given our previous findings that labor market momentum has a dampening or amplifying effect on monetary policy shocks, we now turn to study the implications of these results for the design ofmonetarypolicyfollowingstandardmonetarypolicyrules. Toaddressthis,weuseacalibrated Taylor rule to estimate the projected policy rate under scenarios that account for heterogeneity in labor market momentum. More concretely, we use the coefficients for the monetary policy shock and its interaction with labor market momentum from our previous local projection analysis to generate inflation and unemployment series under two specifications: 1) a baseline scenario that omits our labor market momentum indicator and 2) and additional scenario where labor market momentum is one standard deviation above its mean value—identified as the positive momentum scenario. For this analysis, we use a one-unit standardized monetary policy shock, or roughly 28 basis points. We use these inflation projections within the context of a standard inertial Taylor rule to determine the appropriate policy rate: log(R )−log(R¯) = ϕ (log(R )−log(R¯))+(1−ϕ )[ϕ (log(π )−log(π¯))]+εR (3) t R t−1 R π t t whereϕ istheresponseparametertoinflation, ϕ istheresponseparametertopastvalues π R ofthepolicyrate,R¯ isanestimateoftheneutralrate,andπ¯ istheinflationtarget. εR represents t the i.i.d. monetary policy shock. We assume an inflation target of 2 percent in all scenarios, with response coefficients ϕ = π 1.4 and ϕ = 0.8, in line with standard estimates the literature (Taylor, 1999). We also assume, R for simplicity, that monetary policy is at the neutral rate in the initial period. Given the high degree of uncertainty surrounding the true value of the neutral rate, we repeat the exercise for several values of the neutral rate between 1.75 and 3 percent, in line with recent estimates from the European Central Bank (Brand et al., 2025). 14

Figure 7: Impulse responses to a monetary policy shock and implied Taylor Rule (a) Monetary Policy Shock (b) Inflation (c) Unemployment (d) Policy Rates The results in Figure 7 shows that inflation (panel 7b) under the assumptions of positive labor market momentum is higher than under negative labor market momentum over the rate setting horizon, with the gap largest 4 to 5 quarters after the initial shock. Unemployment (panel 7c), as expected, is persistently lower under the assumption of positive labor market momentum. Assuming an initial policy rate of two percent, the expected policy rate in the positive labor market momentum scenario is persistently higher (panel 7d). After four quarters, the expected policy rate under the inertial Taylor rule for the positive-momentum scenario is 11-36 basispointshigherthanthebaselinescenarionotincorporatinglabormarketmomentum. These results imply that failure to account for the state of momentum in the labor market may, in the case of positive labor market momentum, lead to a monetary policy path that meaningfully undershoots the appropriate level of the policy rate. We finalize this section by testing the robustness of these results to the choice of the neutral rate of the economy. We study the policy response when the neutral rate is 1.75, 2.25, and 3 percent, as there exists significant uncertainty about the value of this rate and variation over 15

time (see, for example, Benigno et al. (2024) and Ferreira and Shousha (2023)). The results are presented in Figure 8. Our results show that even for these different values in neutral rates, accounting for high momentum leads to different policy rate paths, with larger differences at higher nominal neutral rates. All in all, this section has documented the importance of taking into account labor market health and direction, accounted for by our momentum estimator, for policy makers. Even in the presence of policy tightening, high momentum can dampen the response of unemployment and inflation, reducing the effectiveness and transmission of monetary policy to the economy. Figure 8: Estimated Policy Rates: Robustness for Additional Neutral Rate Specifications (a) Neutral rate: 1.75 percent (b) Neutral rate: 2.25 percent (c) Neutral rate: 3 percent 4.3 Measuring slack and the Phillips Curve Our last analysis comprises the comparison of standard measures of labor market slack, such as the unemployment rate or the unemployment gap, and those emerging from our indicators. First, we start by comparing the health of the labor market–the unemployment rate–to the one that the additional series summarized in the two indicators generate. We then turn to analyze what the differences across these series represent when assessing the usual relationship between the labor market and inflation via a standard Phillips Curve. We show that by incorporating additional labor market information, slack changes relative to standard measures, leading to a steeper Phillips Curve. 16

4.3.1 How much slack is there? In order to evaluate the extent to which the official unemployment rate may be under or overstating broader labor market conditions, we compare the euro-area unemployment rate to the one predicted by our labor market indicators. In our approach, we predict a model-based unemployment rate by regressing the actual unemployment rate on activity, momentum, and an interaction of the two. Figure 9: Labor Market Indicators Based Unemployment Rate Figure 9 shows the official unemployment rate compared to the indicator-based unemployment rate (EALMI). We see that during the Eurozone crisis, labor market conditions had not deteriorated as severely as implied by the official unemployment rate, since employment and labor force had declined some, but not as sharply as the unemployment rate increased. In contrast, during the COVID-19 crisis, conditions were somewhat worse than the official rate indicated. Particularly important to this period were the rise of short-term work and labor hoarding, which both suppressed the unemployment rate despite significant weaknesses in the labor market. More recently, labor market conditions have been tighter than the official unemployment rate would signal, as employment and labor force participation are at decades-high levels, although conditions seem to have plateaued and the official rate is converging to the predicted one. This example illustrates the importance of looking at a myriad of labor market estimators rather than just one to obtain a better narrative of the state and direction of the labor market. 4.3.2 Implications for Phillips Curve measurement We next turn to illustrate how the differences between the official unemployment rate and the predicted rate based on the model can result in different empirical correlations between inflation measuresandlabormarketslack,betterknownasthePhillipscurverelationship(Phillips,1958). The Phillips Curve establishes that periods of lower unemployment are associated with higher inflation, and consequently, the evolution of both series is intertwined, generating an empirical trade-off of great interest to central banks. In our exercise, we estimate a linear Phillips Curve for 12-month headline inflation changes atthequarterlyleveland12-monthchangesinnominalcompensationagainstvariousmeasuresof 17

labor market slack: 1) the naive quarterly measures of slack given by the official unemployment rate and the predicted rate by our model; 2) the quarterly unemployment gap, calculated as the difference between the measures in 1) and the trend of unemployment extracted using a Hodrick-Prescott filter; and 3) the annual unemployment gap, defined as the difference between the end-of-year measures in 1) and the European Commission’s annual non-accelerating wage rate of unemployment (NAWRU) for the euro area. Table 2 presents the slope estimates for these specifications, underscoring that the modelbasedunemploymentrateexhibitsastrongernegativerelationshipwithinflationthantheofficial unemployment-basedmeasuresofslack. Wechoosespecification(2)asourpreferredspecification to visually present and interpret our results next. Headline Inflation Nominal Compensation (1) (2) (3) (1) (2) (3) PC Slope: Official UR Coefficient −0.59∗∗∗ −0.95∗∗ −0.59∗ −0.49∗∗∗ −0.47 −0.52∗∗∗ Std. Error (0.11) (0.40) (0.36) (0.08) (0.31) (0.16) PC Slope: Model-based UR Coefficient −0.72∗∗∗ −1.37∗∗∗ −1.11∗∗∗ −0.60∗∗∗ −0.89∗∗∗ −0.87∗∗∗ Std. Error (0.11) (0.36) (0.42) (0.08) (0.28) (0.17) t statistics in parentheses ∗ p<0.10, ∗∗ p<0.05, ∗∗∗ p<0.01 Note. Column (1) refers to the specification using the naive unemployment rate as regressor, (2) refers to the specification using the HP-filtered unemployment rate to compute the unemployment gap, and (3) uses the European Commission NAWRU to compute the annual unemployment gap. Table 2: Phillips Curve Estimates: Official vs. Model-Based Unemployment Rates We present in Figure 10 the historical quarterly relationship between inflation (panel 10a andnominalcompensation(panel10b)againsttheofficialunemploymentrateandthepredicted unemployment rate difference relative to the unemployment rate trend (unemployment gap) extracted using a Hodrick-Prescott filter for 2004:Q2-2024:Q4. A positive gap implies that the unemployment rate (official or model-based) is above trend and negative otherwise. The official unemploymentratetendstopredicthigherslackthanthemodel-basedrate,basedonthenumber of observations on the left of both panels. Similarly, the model-based rate seems to assume less slack than the official rate, as it incorporates additional variables, such as labor hoarding, as explained earlier. These differences explain the higher slope of the Phillips curve when using the model-based rate. 13 As a result, our model-based unemployment rate predicts higher levels of inflation for lower levels of unemployment compared to what the official rate indicates. Similarly to the results shown with the local projections, this is of great importance when assessing how inflation transmits through the economy, second-round effects into wages, and the role of monetary policy. Overall, the applications presented in this paper show that only focusing on one labor market indicator, such as the official unemployment rate, can understate the degree of labor market slack and affect inflation dynamics. 13Thehigherslopeattheleft-endofthegapsuggeststheexistenceofanon-linearfitting,ashasbeenrecently discussed for instance in Crust et al. (2023). 18

Figure 10: Measures of Phillips Curve (a) Headline inflation (b) Nominal Compensation inflation Note. Ugap stands for Unemployment Gap and it is calculated as the difference between the measure of unemployment depicted and the trend obtained from applying a Hodrick-Prescott filter to the quarterly unemployment rate. 5 Conclusion This study introduced a novel approach to assessing euro area labor market conditions through the development of two indicators: level and momentum. We combined information from 22 labormarketvariablesusingprincipalcomponentanalysistocreateacomprehensiveandforwardlooking analysis of labor market dynamics. Our indicators, particularly the momentum indicator, are successful in predicting changes in unemployment rates and capturing the influence of labor market conditions on monetary policy transmission. Our research reveals that labor market momentum significantly affects the impact of monetary policy shocks on inflation and unemployment. High labor market momentum tends to dampen the effects of monetary tightening, suggesting that policymakers should consider this factor when setting policy rates to achieve desired outcomes. Moreover, our model-based measures of labor market slack show a stronger negative relationship with inflation compared to official unemployment-based measures, indicating that reliance solely on the official unemployment rate may understate true labor market health and its impact on inflation. We believe there is a fruitful research agenda stemming from the findings in this paper. One could apply our findings to conduct cross-country analysis within the euro area to examine potential heterogeneity in labor market dynamics and its implications for national and areawide policies. Additionally, our level and momentum indicators could be integrated into central bank forecasting models to enhance their predictive power for key macroeconomic variables and structural factors driving labor market momentum. These research directions can deepen our understanding of labor market dynamics and provide valuable tools for policymakers in an increasingly complex economic environment. 19

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A Appendix A: Data sources and estimation details Table A.1: Labor Market Indicators: Baseline Model Indicator Country Start date End date Source Unemployment rate EA20 2000:Q1 2024:Q1 Eurostat, Haver Unemployment + Underemployment rate EA20 2008:Q1 2024:Q4 Eurostat, Haver Long-term unemployment rate EA20 2009:Q1 2024:Q4 Eurostat, Haver Underemployed part-time workers EA20 2009:Q1 2024:Q4 Eurostat, Haver SPF Unemployment Rate: 8 months EA20 1999:Q1 2025:Q2 Eurostat, Haver Participation rate (15-74) EA20 2009:Q1 2024:Q4 Eurostat, Haver Employment rate (15-74) EA20 2009:Q1 2024:Q4 Eurostat, Haver Employment-Population ratio EA20 2009:Q1 2024:Q4 Eurostat, Haver Temporary employment rate EA20 2009:Q1 2024:Q4 Eurostat, Haver Employment-Unemployment flows EA20 2010:Q2 2024:Q4 Eurostat, Haver Unemployment-Employment flows EA20 2010:Q2 2024:Q4 Eurostat, Haver Hours worked per person employed EA20 2000:Q1 2024:Q4 Eurostat, Haver Hours worked: Industry ex construction EA20 2000:Q1 2024:Q4 Eurostat, Haver Job vacancy rate EA20 2006:Q1 2024:Q4 Eurostat, Haver HCOB PMI: Manufacturing employment EA20 1997:Q2 2025:Q2 S&P Global, Haver HCOB PMI: Services employment EA20 1998:Q3 2025:Q2 S&P Global, Haver Employment expectations EA20 1985:Q1 2025:Q2 EC, Haver Labor Hoarding EA20 2001:Q1 2025:Q2 EC Kurzarbeit Notices Germany 2008:Q1 2025:Q1 FEA, Haver Workers actively seeking work France 1996:Q1 2025:Q1 MdT, Haver Registered Unemployment Spain 1990:Q1 2025:Q1 SEPE,Haver Cassa Integrazione Italy 2009:Q1 2024:Q1 INPS, Haver Note. EC stands for European Commission, FEA for Federal Employment Agency, MdT for Ministre du Travail,SEPEforServicioPublicodeEmpleoEstatal,andINSPforIstitutoNazionaleProvidenzaSociale. Table A.2: Labor Market Indicators: Additional Sources Indicator Country Start date End date Source Job vacancy rate: non-agricultural EA20 2004:Q2 2020:Q3 Eurostat, Haver Labor Hoarding Germany 2001:Q1 2025:Q2 EC Note. EC stands for European Commission. 22

Table A.3: Eigenvalue Analysis of Components Component 1 2 3 4 5 6 7 8 9 10 Eigenvalue 12.46 5.79 1.65 0.88 0.52 0.28 0.15 0.08 0.05 0.04 Proportion 0.57 0.26 0.08 0.04 0.02 0.01 0.01 0.00 0.00 0.00 Cumulative 0.57 0.83 0.90 0.94 0.97 0.98 0.99 0.99 0.99 1.00 Table A.4: Rotated Component Loadings Variable Component 1 Component 2 Unexplained HCOB PMI: Manufacturing employment -0.020 0.313 0.421 HCOB PMI: Services employment 0.083 0.356 0.080 Hours worked per person employed -0.141 0.328 0.226 Hours worked: Industry ex construction 0.154 0.278 0.142 Job vacancy rate 0.265 0.025 0.122 Participation rate (15-74) 0.246 0.075 0.181 Employment rate (15-74) 0.284 0.006 0.012 Employment-Unemployment flows 0.267 0.052 0.077 Unemployment-Employment flows 0.256 0.065 0.133 Employment-Population ratio 0.284 -0.003 0.016 Unemployment + Underemployment rate 0.284 0.016 0.028 Unemployment rate 0.285 0.038 0.026 Underemployed part-time workers 0.259 -0.089 0.189 SPF Unemployment Rate: 8 months 0.278 0.024 0.038 Workers actively seeking work -0.129 0.016 0.802 Registered Unemployment 0.275 0.032 0.046 Kurzarbeit Notices -0.040 0.358 0.244 Cassa Integrazione 0.043 0.338 0.254 Long-term unemployment rate 0.279 -0.094 0.063 Temporary employment rate -0.164 -0.253 0.388 Labor Hoarding -0.047 0.381 0.144 Employment Expectations Indicator 0.108 0.326 0.128 23

B Appendix B: Business Cycle Robustness Checks Weperformseveralrobustnesschecksonourmomentumindicatoracrossdifferentsamplelengths and lag specifications, as well as against multiple forward-looking labor market indicators. Figure 11 shows the in-sample prediction over the entire sample, including the post-COVID period. This specification includes dummy variables for the several COVID periods reflected in the series. Our LMI predictor (RMSE = 0.143) performs essentially the same as the European Commission’s employment expectations indicator (RMSE = 0.142). Under this specification, we see that the fit is particularly poor at the beginning of the sample as the model tries to fit the large swings in the COVID period, even with the dummy variable specification, leading us to focus most of our analysis on the pre-COVID period. Figure 11: In-Sample Prediction: Full Sample (a) 1-lag (b) 2-lag Note. Dataextendfrom2011Q1through2025Q1. LMIstandsfortheeuro-areaMomentumLaborMarket Indicator developed in this paper, EEI for the European Commission’s Employment Expectations Indicator. The sample focusing on the pre-COVID period (Figure 12) performs much better for both indicators towards the beginning of the sample, with LMI (RMSE = 0.165) outperforming EEI (RMSE = 0.172). Figure 12: In-Sample Prediction: Pre-COVID Short Sample (a) 1-lag (b) 2-lag Note. Dataextendfrom2011Q1through2019Q4. LMIstandsfortheeuro-areaMomentumLaborMarket Indicator developed in this paper, EEI for the European Commission’s Employment Expectations Indicator. 24

WefurthertestourlabormarketindicatoragainsttheEuropeanLabourMarketBarometer (LMB). Due to the shorter series of the LMB, we truncate our LMI series for this analysis to ensure comparability of sample periods over the forecast. Figure 13 shows that our LMI model predictions (RMSE = 0.15) again outperform the LMB model (RMSE = 0.176). Figure 13: In-Sample Prediction: European Labor Market Barometer (LMB) (a) 1-lag (b) 2-lag Note. Dataextendfrom2012Q1through2019Q4. LMIstandsfortheeuro-areaMomentumLaborMarket Indicator developed in this paper. We also test our momentum indicator against the unemployment component (Comp A) of theLMBtoassurethatmomentum’srelativeperformanceoverLMBisnotdrivenbycomponents unrelated to our dependent variable. Figure 14 shows that visually, Comp A fails to generate meaningful predictions of changes in the unemployment rate in our model setting. Figure 14: In-Sample Prediction: Component A of LMB (a) 1-lag (b) 2-lag Note. Dataextendfrom2009Q3through2019Q4. LMIstandsfortheeuro-areaMomentumLaborMarket Indicatordevelopedinthispaper,EEIfortheEuropeanCommission’sEmploymentExpectationsIndicator. 25

C Appendix C: Additional Local Projection Responses Figure 15: Local projection analysis: Labor Force Rate (a) Average Effect (b) Dampening Effect Note. Lightshadedareasrepresent90percentconfidenceintervals,darkshadedareasrepresent68percent confidence intervals, and the solid line represents the mean value. Figure 16: Local projection analysis: Hours worked per employee (a) Average Effect (b) Dampening Effect Note. Hours worked per person employed are expressed in log growth rates. Light shaded areas represent 90 percent confidence intervals, dark shaded areas represent 68 percent confidence intervals, and the solid line represents the mean value. Figure 17: Local projection analysis: Nominal Compensation per Employee (a) Average Effect (b) Dampening Effect Note. Nominalcompensationperemployeeareexpressedinloggrowthrates. Lightshadedareasrepresent 90 percent confidence intervals, dark shaded areas represent 68 percent confidence intervals, and the solid line represents the mean value. 26