Abstract
For policy institutions such as central banks, it is important to have a timely and accurate measure of past and current economic activity and the business cycle situation. The most prominent example for such a measure is gross domestic product (GDP). However, GDP is only released at a quarterly frequency and with a substantial delay. Furthermore, it captures elements that are not directly linked to the business cycle and the underlying momentum of the economy. In this paper, I construct a new business cycle index for the Swiss economy, which uses state-of-the-art methods, is available at a monthly frequency and can be calculated in real-time, even when some indicators are not yet available for the most recent periods. The index is based on a large and broad set of monthly and quarterly indicators. As I show, for the case of Switzerland, it is important to base a business cycle index on a broad set of indicators instead of only a small subset. This result confirms the findings of a previous study on tracking short-term economic developments in Switzerland and is in contrast with the results for other countries.
Similar content being viewed by others
Notes
An alternative would be that the quarterly level equals the level at the last day of the respective quarter. However, in the context of business cycle analysis this would not be appropriate since such an aggregation would miss temporary shocks that have occurred during the quarter. Furthermore, quarterly surveys usually ask about quarterly averages and not end-of-quarter values.
Note that in Mariano and Murasawa (2003) or Banbura et al. (2013), the monthly flow series are included as monthly (and not 3-month) changes. In this case, the aggregation rule for the quarterly flow variables would change to \(G^f(L) = \frac{1}{3} + \frac{2}{3} L + \frac{3}{3} L^2 + \frac{2}{3} L^3 + \frac{1}{3} L^4 \). However, applying their aggregation rule leads to inferior forecasting results for Switzerland, as shown in Galli et al. (2018) Therefore, I apply the aggregation rule proposed by Angelini et al. (2011).
Note the number of lags in the VAR of the factors has a negligible impact on the in-sample part of the model, it mainly matters for the out-of-sample part (which is not used for a business cycle indicator). The reason for this is that, in the context of a large-scale version of the factor model, the noise in the transition equation weighs to heavy compared to the strong signals from the data as soon as for the particular period enough observations are available (i.e., for the in-sample part of the model).
The minimum sample length for the balanced data set is set to 15 years.
Note that the reason for not having to distinguish between quarterly flow and stock variables when estimating the variances is that our quarterly flow variables enter in 3-month growth changes. In the case of month-on-month growth rates, we would have that \(V[{\tilde{u}}_{i,t}] = V[G^f(L) u_{i,t}] = \frac{1}{9}V(u_{i,t}) + \frac{4}{9}V(u_{i,t-1}) + \frac{9}{9}V(u_{i,t-2}) + \frac{4}{9}V(u_{i,t-3}) + \frac{1}{9}V(u_{i,t-4}) = \frac{3}{9} V(u_t)\). Therefore, \(V(u_{i,t}) = \frac{9}{3} V({\tilde{u}}_{i,t})\).
For numerical reasons (R must be invertible), we replace the upper left element of R by \(c I_{n^Q}\) for \(t \neq 3,6,9,...\), where c is fixed and a very small number, see Neusser (2011), p. 250.
My approach follows Mariano and Murasawa (2003). Alternatives, such setting these observations to non-available, would yield the same results as these observations are skipped by the Kalman filter.
A possibility would be to use GDP as the target variable for the selection of relevant indicators. However, this could potentially yield a set of indicators that are particularly good at explaining quarterly volatility in GDP but not the business cycle. Examples would be indicators that cover public spending, the health sector or sectors that are less linked to the overall business cycle.
Indicators not available on a seasonally adjusted basis are calendar-, seasonally- and outlier-adjusted using the X-13ARIMA-SEATS procedure.
Note that the recession dates from Siliverstovs (2013) were based on quarterly GDP figures released in September 2012, which did not yet include the ESA2010 benchmark GDP revision implemented in 2014.
Note that there is a potential structural break in the GDP series since the ESA2010 benchmark GDP revision was only implemented back to 1995. Since the business cycle index parameters are based on a balanced sample that only includes the revised part of the GDP series, the BCI values for the pre-1995 period should be treated with caution.
Following Banbura and Ruenstler (2011), weights related to missing data are set to zero.
Note that this procedure ignores potential correlation across factors, which could influence the indicators’ weights for the business cycle index. One solution would be to include the BCI, i.e., the fitted value for GDP, in the state vector. However, in our case the correlations between the factors are comparatively low, so that influence of the weights should be limited.
The legend for the acronyms of the 30 most important indicators can be found in Table 3 in the “Appendix”.
Revisions of past data may be due to updated indicator estimates provided by the statistical agencies or due to revisions stemming from the seasonal adjustment procedure.
Note that since the BCI is obtained using the fitted value for GDP, \(E[BCI_t | \cdot ]\) actually equals \(E[gdp_t | \cdot ]\).
Note that in this context, the term "accuracy” does not mean closeness to a specific target (since this target, the business cycle, is unobserved in our case). It is more a measure of finality of the index value for a particular month, measuring how much information is already incorporated for this month and the potential for revisions.
Given that our business cycle index is the GDP-weighted sum of four factors, such revisions in GDP potentially also affect the business cycle index by changes in the factor loadings of GDP.
References
Abberger, K., Graff, M., Siliverstovs, B., & Sturm, J.-E. (2014). The KOF economic barometer, version 2014: A composite leading indicator for the swiss business cycle, KOF working paper series, 353.
Altissimo, F., Bassanetti, A., Cristadoro, R., Forni, M., Lippi, M., Reichlin, L., & Veronese, G. (2001). Eurocoin: A real time coincident indicator of the euro area business cycle, CEPR Discussion Paper Series, 3108.
Altissimo, F., Cristadoro, R., Forni, M., Lippi, M., & Veronese, G. (2010). New EuroCOIN: Tracking economic growth in real time. The Review of Economics and Statistics, 92, 1024–1034.
Alvarez, R., Camacho, M., & Perez-Quiros, G. (2016). Aggregate versus disaggregate information in dynamic factor models. International Journal of Forecasting, 32, 680–694.
Angelini, E., Camba-Mendez, G., Giannone, D., Reichlin, L., & Rünstler, G. (2011). Short-term forecasts of euro area GDP growth. Econometrics Journal, 14(1), C25–C44.
Aruoba, S. B., Diebold, F. X., & Scotti, S. (2009). Real-time measurement of business conditions. Journal of Business and Economic Statistics, 27, 417–427.
Bai, J. (2003). Inferential theory for factor models of large dimensions. Econometrica, 71, 135–171.
Banbura, M., Giannone, D., Modugno, M., & Reichlin, L. (2013). Now-casting and the real-time data flow. In: Elliot, G., & Timmermann, A. (Eds)., Handbook of economic forecasting (vol. 2A, chap. 4, pp. 195–237). Amsterdam: Elsevier.
Banbura, M., & Modugno, M. (2014). Maximum likelihood estimation of factor models on data sets with arbitrary pattern of missing data. Journal of Applied Econometrics, 29, 133–160.
Banbura, M., & Ruenstler, G. (2011). A look into the factor model black box: Publication lags and the role of hard and soft data in forecasting GDP. International Journal of Forecasting, 27, 333–346.
Bernanke, B., & Boivin, J. (2003). Monetary policy in a data-rich environment. Journal of Monetary Economics, 50, 525–546.
Boivin, J., & Ng, S. (2006). Are more data always better for factor analysis? Journal of Econometrics, 132, 169–194.
Camacho, M., & Perez-Quiros, G. (2010). Introducing the euro-sting: Short-term indicator of euro area growth. Journal of Applied Econometrics, 25, 663–694.
Crone, T. M., & Clayton-Matthews, A. (2005). Consistent economic indexes for the 50 states. Review of Economics and Statistics, 87, 593–603.
Doz, C., Giannone, D., & Reichlin, L. (2011). A two-step estimator for large approximate dynamic factor models based on Kalman filtering. Journal of Econometrics, 164, 188–205.
Doz, C., Giannone, D., & Reichlin, L. (2012). A quasi-maximum likelihood approach for large, approximate dynamic factor models. The Review of Economics and Statistics, 94, 1014–1024.
Durbin, J., & Koopman, S . K. (2012). Time series analysis by state space models. Oxford: Oxford University Press.
Forni, M., Hallin, M., Lippi, M., & Reichlin, L. (2000). The genegeneral dynamic factor model: Identification and estimation. The Review of Economics and Statistics, 82, 504–554.
Forni, M., Hallin, M., Lippi, M., & Reichlin, L. (2001). Coincident and leading indicators for the euro area. The Economic Journal, 111, 62–85.
Frale, C., Marcellino, M., Mazzi, G., & Prioetti, T. (2010). Survey data as coincident or leading indicators. Journal of Forecasting, 29, 109–131.
Galli, A., Hepenstrick, C., & Scheufele, R. (2017). Mixed-frequency models for tracking economic developments in Switzerland, SNB working paper series, 2017-2.
Galli, A., Hepenstrick, C., & Scheufele, R. (2018). Mixed-frequency models for tracking economic developments in Switzerland. International Journal of Central Banking (forthcoming).
Giannone, D., Reichlin, L., & Small, D. (2008). Nowcasting: The real-time informational content of macroeconomic data. Journal of Monetary Economics, 55, 665–676.
Hamilton, J. D. (1994). Time series analysis. Princeton, NJ: Princeton University Press.
Koopman, S. J., & Harvey, A. (2003). Computing observation weights for signal extraction and filtering. Journal of Economic Dynamics & Control, 27, 1317–1333.
Lopes, H. F., & West, M. (2004). Bayesian model assessment in factor analysis. Statistica Sinica, 14, 41–67.
Luetkepohl, H. (2005). New introduction to multiple time series analysis. New York: Springer.
Mariano, R. S., & Murasawa, Y. (2003). A new coincident index of business cycles based on monthly and quarterly series. Journal of Applied Econometrics, 18, 427–443.
Mariano, R. S., & Murasawa, Y. (2010). A coincident index, common factors, and monthly real gdp. Oxford Bulletin of Economics and Statistics, 72, 27–46.
Matheson, T. (2011). New indicators for tracking growth in real time. IMF working paper, 11/43.
Matheson, T. D. (2012). Financial conditions indexes for the United States and euro area. Economics Letters, 115, 441–446.
Neusser, K. (2011). Zeitreihenanalyse in den Wirtschaftswissenschaften (3rd ed.). Wiesbaden: Vieweg + Teubner.
Schumacher, C., & Breitung, J. (2008). Real-time forecasting of German GDP based on a large factor model with monthly and quarterly data. International Journal of Forecasting, 24, 386–398.
Siliverstovs, B. (2013). Dating business cycles in historical perspective: Evidence for Switzerland. Journal of Economics and Statistics, 233, 661–679.
Song, J., & Belin, T. R. (2008). Choosing an appropriate number of factors in factor analysis with incomplete data. Computational Statistics and Data Analysis, 52, 3560–3569.
Stock, J. H., & Watson, M. W. (2002a). Forecasting using principal components from a large number of predictors. Journal of the American Statistical Association, 97, 1167–1179.
Stock, J. H., & Watson, M. W. (2002b). Macroeconomic forecasting using diffusion indexes. Journal of Business & Economic Statistics, 20, 147–162.
Stock, J. H., & Watson, M. W. (2011). Dynamic factor models. In: Clements, M. P., Hendry, D. F. (Eds). The Oxford handbook of economic forecasting (chap. 7, pp. 35–59). Oxford: Oxford University Press.
The Conference Board (2001). Business cycle indicators handbook.
Acknowledgements
I want to thank Marta Banbura, Gregor Bäurle, Christian Hepenstrick, Daniel Kaufmann, Matthias Lutz, Massimiliano Marcellino, Klaus Neusser, Alexander Perruchoud, Rolf Scheufele, three anonymous referees, as well as the participants at the 2016 CIRET conference in Copenhagen and the SNB brownbag workshop for valuable comments. The views, opinions, findings, and conclusions or recommendations expressed in this paper are strictly those of the author. They do not necessarily reflect the views of the Swiss National Bank. The SNB takes no responsibility for any errors or omissions in, or for the correctness of, the information contained in this paper.
Author information
Authors and Affiliations
Corresponding author
Appendices
Appendix A: The Kalman Filter
Following Hamilton (1994), for our state space model
the Kalman filter applied with the parameters \(\theta = \begin{bmatrix} \Lambda ^*&\Phi&\Sigma _{vv}&\Sigma _{ww} \end{bmatrix}'\) provides a time series of filtered states \({\{\xi _{i|i}\}}_{i=1}^T\) and their covariance matrices \({\{P_{i|i}\}}_{i=1}^T\). The Kalman smoother provides a time series of the smooth correspondences, \({\{\xi _{i|T}\}}_{i=1}^T\) and \({\{P_{i|T}\}}_{i=1}^T\).
1.1 Details on the Kalman procedure
First we define:
-
\(\xi _{t|t-1} = E[\xi _{t}| {\{y_i\}}_{i=1}^{t-1}]\), the forecast for \(\xi _t\) given data on y up to \(t-1\)
-
\(y_{t|t-1} = E[y_{t}| {\{y_i\}}_{i=1}^{t-1}]\), the forecast for \(y_t\) given data on y up to \(t-1\)
-
\(P_{t|t-1} = Var(\xi _{t}| {\{y_i\}}_{i=1}^{t-1})\), the covariance matrix of \(\xi _t\)
-
\(\xi _{t|t} = E[\xi _{t}|{\{y_i\}}_{i=1}^t]\), the update for \(\xi _t\) given all information up to t
-
\(P_{t|t} = Var(\xi _{t}| {y_i\}}_{i=1}^{t})\), the covariance of \(\xi _t\) given all information up to t
Given our parameters \(\theta \), the Kalman filter is then just an application of theorems on two variables (in our case \(\xi \) and y) that are jointly normal distributed. The estimation proceeds as follows:
-
Step 1, forecasting \(\xi _t\): \(\xi _{t|t-1} = F \xi _{t-1|t-1}\)
-
Step 2, variance of forecast for \(\xi _t\): \(P_{t|t-1} = F P_{t-1|t-1} F' + Q \)
-
Step 3, forecasting \(y_t\): \(y_{t|t-1} = H_t \xi _{t|t-1}\)
-
Step 4, variance of forecast for \(y_t\): \(S_t = H_t P_{t|t-1} H_t' + R\)
-
Step 5, forecast error of \(y_t\): \(z_t = y_t - y_{t|t-1}\)
-
Step 6, updating \(\xi _t\): \(\xi _{t|t} = \xi _{t|t-1} + P_{t|t-1} H'_t S_t^{-1} z_t\)
-
Step 7, variance of update for \(\xi _t\): \(P_{t|t} = P_{t|t-1} - P_{t|t-1} H'_t S_t^{-1} H_t P_{t|t-1} \)
-
Step 8, Kalman gain: \(K_t = F P_{t|t-1} H'_t S_t^{-1}\)
-
Do the same for \(\{\xi _{t+1}, P_{t+1}\}\), \(\{\xi _{t+2}, P_{t+2}\}\), and so on.
The result is a time series of filtered states \({\{\xi _{i|i}\}}_{i=1}^T\) and their covariance matrices \({\{P_{i|i}\}}_{i=1}^T\). In the filtered observation vector, missing values have been filled by the Kalman filter.
1.1.1 Details on the Smoothing Procedure
From the Kalman filter, we obtain estimates of \(\xi _{t|t-1}\) and \(P_{t|t-1}\) (the forecasts, based on past information) as well as of \(\xi _{t|t}\) and \(P_{t|t}\) (the updates, based on past and current information) for each time period 1 to T. Starting with \(\xi _{T|T}\) (the update for the last time period), we can go backwards to smooth our estimates by also incorporating future estimates and information, i.e., the estimation error for the next period given all information.
For \(t=T\), the smoothed estimate is simply given by the filtered state, i.e.
and for \(t<T\) by
The result is a time series of smoothed states \({\{\xi _{i|T}\}}_{i=1}^T\). The mean squared error (MSE) of the smoothed states \(\xi _{t|T}\) is given by
Appendix B
Rights and permissions
About this article
Cite this article
Galli, A. Which Indicators Matter? Analyzing the Swiss Business Cycle Using a Large-Scale Mixed-Frequency Dynamic Factor Model. J Bus Cycle Res 14, 179–218 (2018). https://doi.org/10.1007/s41549-018-0030-4
Received:
Accepted:
Published:
Issue Date:
DOI: https://doi.org/10.1007/s41549-018-0030-4