Abstract
The measurement of the sources of economic growth, essential for understanding the long-term perspective of any economy, depends on both the functional form that summarizes technology and factor share values. We estimate the share of physical capital in output, implied by a Cobb–Douglas production function, using fully modified and dynamic ordinary least squares estimators within a panel cointegration framework for 109 countries over the period 1960–2014. For several measures of labor, our estimates range between 0.46 and 0.56 for the worldwide set and vary significantly across regions. The panel estimates are: (i) similar when human capital is taken as a separate factor of production; and (ii) more robust than both the average of the individual cross-country estimates and those obtained in the model in differences. We also find that the CES production function estimates favor the Cobb–Douglas specification. Finally, we provide some evidence of a decline in the share of labor, in line with recent empirical studies.
Similar content being viewed by others
Notes
García-Verdú (2005) proposes a method for estimating the labor and capital factor shares by using cross-sectional household survey data containing detailed information on household income by source in Mexico.
Elias (1992) considers a production function model with a deterministic trend and dummy variables.
Senhadji (2000) considers a production function with constant returns to scale and employs the fully modified OLS estimator.
The first-difference operator eliminates low frequencies and therefore emphasizes the short-term fluctuations contained in the data.
The parameter describing the share of physical capital in output is typically set to the benchmark value of \(1/3\approx 0.33\), as suggested by the national income accounts of some industrial countries.
In most countries, the level of productivity (measured as a Solow residual by the Penn World Table) has been growing at a positive rate, and we therefore expect a trend in the productivity level. Nonetheless, low-income economies may have had poor productivity performance, in which case the parameter \(\rho _i\), the growth rate of productivity, should be zero.
Quality appears in the accumulation of capital equation, which means that quality appears as a form of technological progress specific to investment. The idea is that when the quality of capital increases, more goods can be produced from physical capital by giving up one unit of output or consumption.
Several developing countries experienced periods of high inflation during the 1980s (for example, Argentina, Bolivia and Peru reached inflation rates of 3080, 11,750 and 7841 percent, respectively), and this leads to considerable distortion in the price variables.
Specifically, in the construction of the new test statistic, instead of subtracting the individual mean, the first observation is subtracted. As a result, unlike the test proposed by Levin et al. (2002), the Breitung (2001)’s test is unbiased (i.e., the proposed t-statistic exhibits zero mean) and very robust to the lag augmentation.
The group mean panel cointegration tests are based upon the average of their components. As a consequence, the asymptotic results are derived from the limiting distribution of the numerator and denominator average rather than the average of all of the statistics.
Hoang (2006) shows, through simulation experiments, that the McCoskey and Kao tests have good power when the number of time observations is greater than 100. When the number of time observations is less than or around 50, these tests do not exhibit good power.
It is worth mentioning that in Table 4 the share of capital estimates is statistically significant.
The GDP per capita and the capital/output ratio are averages over time (1960–2014) and across countries within each region.
As indicated in Table 2, all variables in first differences are stationary variables. Even though the FMOLS and DOLS estimation methods were developed for nonstationary data, we estimate Eq. (5) in first differences with those methods in order to make the results comparable to those for the model in levels.
References
Baltagi B, Kao C (2000) Nonstationary panels, cointegration in panels and dynamic panels: a survey. In: Baltagi BH, Fomby BT, Hill RC (eds) Nonstationary panels, panel cointegration, and dynamic panels, advances in econometrics, vol 15. Emerald Group Publishing Limited, Bingley, pp 7–51
Banerjee A (1999) Panel data units roots and cointegration: an overview. Oxf Bull Econ Stat 61(S1):607–629
Barro R, Lee J (2013) A new data set of educational attainment in the world, 1950–2010. J Dev Econ 104:184–198
Bentolila S, Saint-Paul G (2003) Explaining movements in the labor share. Contrib Macroecon 3(1):1–33
Bernanke B, Gürkaynak R (2002) Is growth exogenous? Taking Mankiw, Romer, and Weil seriously. NBER Macroeconomics Annual 2001, vol 16, NBER Books, pp 11–72
Breitung J (2001) The local power of some unit root tests for panel data. In: Baltagi BH, Fomby BT, Hill RC (eds) Nonstationary panels, panel cointegration, and dynamic panels, advances in econometrics, vol 15. Emerald Group Publishing Limited, Bingley, pp 161–177
Choi I (2001) Unit root tests for panel data. J Int Money Finance 20(2):249–272
De Silva S, Hadri K, Tremayne AR (2009) Panel unit root tests in the presence of cross-sectional dependence: finite sample performance and an application. Econ J 12(2):340–366
Elias VJ (1992) Sources of growth: a study of seven Latin American economies. ICS Press, San Francisco
Elsby MWL, Hobjin B, Sahin A (2013) The decline of the U.S. labor share. Brook Pap Econ Act 47(2):1–63
Engle R, Granger C (1987) Cointegration and error correction: representation, estimation and testing. Econometrica 55(2):251–276
Feenstra RC, Inklaar R, Timmer MP (2015) The next generation of the Penn World Table. Am Econ Rev 105(10):3150–3182
García-Verdú R (2005) Factor shares from household survey data. Working papers 2005-05, Banco de México
Gollin D (2002) Getting income shares right. J Polit Econ 110(2):458–474
Greenwood J, Jovanovic B (2001) Accounting for Growth. In: Hulten C, Dean E, Harper M (eds) New developments in productivity analysis. University of Chicago Press, Chicago
Hansen B (1992) Efficient estimation and testing of cointegrating vectors in the presence of deterministic trends. J Econ 53(1–3):87–121
Henningsen A, Henningsen G (2011) Econometric estimation of the constant elasticity of substitution’ function in R: package micEconCES. FOI working paper 2011/9, Institute of Food and Resource Economics, University of Copenhagen
Hoang NT (2006) New tests for cointegration in heterogeneous panels. Working paper 06–09, Department of Economics, University of Colorado at Boulder
Im K, Pesaran M, Shin Y (2003) Testing for unit roots in heterogeneous panels. J Econ 115(1):53–74
Johansen S (1988) Statistical analysis of cointegration vectors. J Econ Dyn Control 12(2–3):231–254
Jorgenson D, Griliches Z (1967) The explanation of productivity change. Rev Econ Stud 34(3):249–283
Kmenta J (1967) On estimation of the CES production function. Int Econ Rev 8(2):180–189
Kao C (1999) Spurious regression and residual-based tests for cointegration in panel data. J Econ 90(1):1–44
Kao C, Chiang MH (2001) On the estimation and inference of a cointegrated regression in panel data. In: Baltagi BH, Fomby BT, Hill RC (eds) Nonstationary panels, panel cointegration, and dynamic panels, advances in econometrics, vol 15. Emerald Group Publishing Limited, Bingley, pp 179–222
Kao C, Chiang MH, Chen B (1999) International R&D spillovers: an application of estimation and inference in panel cointegration. Oxf Bull Econ Stat 61(S1):691–709
Karabarbounis L, Neiman B (2013) The global decline of the labor share. Q J Econ 129(1):61–103
King R, Plosser C, Rebelo S (1988) Production, growth and business cycles: I. The basic neoclassical model. J Monet Econ 21(2–3):195–232
Levin A, Lin CF, Chu CS (2002) Unit root tests in panel data: asymptotic and finite sample properties. J Econ 108(1):1–24
Maddala G, Wu S (1999) A comparative study of unit root test with panel data and a new simple test. Oxf Bull Econ Stat 61(S1):631–652
Mankiw NG, Romer D, Weil DN (1992) A contribution to the empirics of economic growth. Q J Econ 107(2):407–437
Mark N, Sul D (2003) Cointegration vector estimation by panel DOLS and long-run money demand. Oxf Bull Econ Stat 65(5):665–680
Marrocu E, Paci R, Pala R (2001) Estimation of total factor productivity for regions and sectors in Italy. A panel cointegration approach. Rivista Internazionale di Scienze Economiche e Commerciali 48:533–558
McCoskey S, Kao C (1998) A residual-based test of the null of cointegration in panel data. Econ Rev 17(1):57–84
Ndiaye MBO, Korsu RD (2016) Growth accounting in ECOWAS countries: a panel unit root and cointegration approach. In: Seck D (ed) Accelerated economic growth in West Africa. Springer, Berlin, pp 19–35
Pedroni P (1999) Critical values for cointegration test in heterogeneous panels with multiple regressors. Oxf Bull Econ Stat 61(S1):653–670
Pedroni P (2000) Fully modified OLS for heterogeneous cointegrated panels. In: Baltagi BH, Fomby BT, Hill RC (eds) Nonstationary panels, panel cointegration, and dynamic panels, advances in econometrics, vol 15. Emerald Group Publishing Limited, Bingley, pp 93–130
Pedroni P (2001) Purchasing power parity test in cointegrated panels. Rev Econ Stat 83(4):727–731
Pedroni P (2004) Panel cointegration; asymptotic and finite sample properties of pooled time series tests, with an application to the PPP hypothesis. Econ Theory 20(3):597–625
Pesaran MH (2007) A simple panel unit root test in the presence of cross section dependence. J Appl Econ 22(2):265–312
Peretto PF, Seater JJ (2007) Factor-eliminating technical change. J Monet Econ 60(4):459–473
Phillips P (1995) Fully modified least squares and vector autoregression. Econometrica 63(5):1023–1078
Phillips P, Hansen B (1990) Statistical inference in instrumental variables regression with I(1) processes. Rev Econ Stud 57(1):99–125
Phillips P, Moon H (2000) Nonstationary panel data analysis: an overview of some recent developments. Econ Rev 19(3):263–286
Phillips P, Perron P (1988) Testing for a unit root in time series regression. Biometrika 75(2):335–346
Psacharopoulos G (1994) Returns to investment in education: a global update. World Dev 22(9):1325–1343
Saikkonen P (1991) Asymptotically efficient estimation of cointegrating regressions. Econ Theory 7(1):1–21
Sturgill B (2012) The relationship between factor shares and economic development. J Macroecon 34(4):1044–1062
Senhadji A (2000) Sources of economic growth: an extensive growth exercise. IMF Staff Paper 47(1):129–158
Sheng X, Yang J (2013) Truncated product methods for panel unit root tests. Oxf Bull Econ Stat 75(4):624–636
Solow R (1956) A contribution to the theory of economic growth. Q J Econ 70(1):65–94
Stock J, Watson M (1993) A simple estimator of cointegrating vectors in higher order integrated systems. Econometrica 61(4):783–820
Westerlund J (2006) Testing for panel cointegration with multiple structural breaks. Oxf Bull Econ Stat 68(1):101–132
Acknowledgements
This paper is based on chapter 2 of Juan Carlos Aquino’s Ph.D. Dissertation at Washington University in St. Louis. We would like to acknowledge Gaetano Antinolfi, Costas Azariadis, Michele Boldrin, Robert Parks, Witson Peña, Francisco Rodríguez, Gabriel Rodríguez, Badi Baltagi and the three anonymous referees for valuable comments and suggestions. We also thank to the participants of the IX Annual Meeting of the Latin American and Caribbean Economic Association, the XXII Annual Meeting of the Central Bank of Peru, the XX Annual Meeting of the Central Bank of Uruguay and the Research Seminar of the Central Bank of Peru for their discussions and useful comments. Special thanks to Patricia Paskov for proofreading the paper. As usual, all remaining errors are ours.
Author information
Authors and Affiliations
Corresponding author
Additional information
Publisher's Note
Springer Nature remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.
Appendices
A: Regional groups
(see Table 8)
B: Human capital as a separate factor of production
In our setup, human capital is labor augmenting, and so these two factors are “perfect substitutes” in production (i.e., human capital is only a measure of labor quality). Another approach including human capital (H) in a production function considers this variable as a separate factor of production as in Mankiw et al. (1992). For this case, Eq. (3) can instead be written as
where \(\alpha \) and \(\beta \) denote the shares of physical and human capital in output, respectively. Once again, assuming constant returns to scale and perfect competition in factor markets, (6) can be written as
or, equivalently,
Table 9 reports the estimation results for the worldwide and regional sets of countries, for the FMOLS and DOLS estimation methods and for population and employment used labor measures. The results indicate that the share of physical capital ranges from 0.35 to 0.66. For the worldwide sample, the share of physical capital ranges from 0.48 to 0.52. These results are similar to the estimates in Table 4. In most of the cases, the share of human capital estimates for the regional sets is not significant, whereas for the worldwide sample those estimates are significant and range from 0.05 to 0.14.
C: The CES production function model
As is well known, the Cobb–Douglas production function constitutes a particular case of the CES production function. For this more general specification, the implied factor shares are not constant but depend on the factor/output ratio. In order to test for local misspecification, we consider a CES production function with two inputs given by
where \(\theta \) and \(1-\theta \) determine the optimal distribution of inputs, and \(\delta \) determines the (constant) elasticity of substitution (which equals \(\sigma =(1+\delta )^{-1}\)). Under the assumption of competitive markets, the share of capital is given by \(\theta (K/Y)^{-\delta }\) and the share of labor is given by \((1-\theta )(L/Y)^{-\delta }\). Kmenta (1967) proposed an approximation to the classical two-input CES production function
by taking natural logs to both sides of (9) and computing a second-order Taylor expansion to \(\log \{\theta K_{it}^{-\delta } + (1-\theta ) L_{it}^{-\delta }\}\) around \(\delta = 0\). Alternatively, the same expression can be obtained by computing a first-order Taylor expansion to the transformed CES function around \(\delta = 0\) (Henningsen and Henningsen 2011). Substituting (2) into (10) and defining \(\beta =-\frac{\delta }{2}\theta (1-\theta )\) leads to
or, equivalently,
Therefore, by estimating (12) and testing \(H_0:\beta =0\) we can evaluate whether the Cobb–Douglas function constitutes a valid description of the production process. Table 10 reports estimates of \(\beta \) for the worldwide sample, which indicates that \(\{\log (K_{it}/L_{it})\}^2\) is not statistically significant and favors the Cobb–Douglas specification. It should be noted that when we consider the worldwide sample, the estimates are also quite robust since there are enough observations both across countries and years.
Among regional estimates considering different methods and measures of labor, in general, estimates for the industrial and East Asia, South Asia and Pacific regions indicate that we cannot reject the null of \(\beta =0\) in favor of the Cobb–Douglas specification; in the other three regions, most of the estimates indicate that the null is rejected; nonetheless, most of the coefficient estimates are close to zero.
Rights and permissions
About this article
Cite this article
Aquino, J.C., Ramírez-Rondán, N.R. Estimating factor shares from nonstationary panel data. Empir Econ 58, 2353–2380 (2020). https://doi.org/10.1007/s00181-019-01647-y
Received:
Accepted:
Published:
Issue Date:
DOI: https://doi.org/10.1007/s00181-019-01647-y