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Topics in Microeconometrics Professor William Greene Stern School of Business, New York University at Curtin Business Sc PowerPoint Presentation
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Topics in Microeconometrics Professor William Greene Stern School of Business, New York University at Curtin Business Sc

Topics in Microeconometrics Professor William Greene Stern School of Business, New York University at Curtin Business Sc

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Topics in Microeconometrics Professor William Greene Stern School of Business, New York University at Curtin Business Sc

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  1. Topics in Microeconometrics Professor William Greene Stern School of Business, New York University at Curtin Business School Curtin University Perth July 22-24, 2013

  2. 2. Stochastic Frontier Model

  3. Stochastic Frontier Models • Motivation: • Factors not under control of the firm • Measurement error • Differential rates of adoption of technology • Frontieris randomly placed by the whole collection of stochastic elements which might enter the model outside the control of the firm. • Aigner, Lovell, Schmidt (1977), Meeusen, van den Broeck (1977), Battese, Corra (1977)

  4. The Stochastic Frontier Model ui > 0, but vi may take any value. A symmetric distribution, such as the normal distribution, is usually assumed for vi. Thus, the stochastic frontier is +’xi+vi and, as before,ui represents the inefficiency.

  5. Least Squares Estimation Average inefficiency is embodied in the third moment of the disturbance εi= vi - ui. So long as E[vi - ui] is constant, the OLS estimates of the slope parameters of the frontier function are unbiased and consistent. (The constant term estimates α-E[ui]. The average inefficiency present in the distribution is reflected in the asymmetry of the distribution, which can be estimated using the OLS residuals:

  6. Application to Spanish Dairy Farms N = 247 farms, T = 6 years (1993-1998)

  7. Example: Dairy Farms

  8. The Normal-Half Normal Model

  9. Normal-Half Normal Variable

  10. Error Decomposition

  11. Standard Form

  12. Battese Coelli Formulation

  13. Estimation: Least Squares/MoM • OLS estimator of β is consistent • E[ui] = (2/π)1/2σu, so OLS constant estimates α+ (2/π)1/2σu • Second and third moments of OLS residuals estimate

  14. A Possible Problem with theMethod of Moments • Estimator of σu is [m3/-.21801]1/3 • Theoretical m3 is < 0 • Sample m3 may be > 0. If so, no solution for σu. (Negative to 1/3 power.)

  15. Log Likelihood Function Waldman (1982) result on skewness of OLS residuals: If the OLS residuals are positively skewed, rather than negative, then OLS maximizes the log likelihood, and there is no evidence of inefficiency in the data.

  16. Alternative Models:Half Normal and Exponential

  17. Normal-Exponential Log Likelihood

  18. Normal-Truncated Normal

  19. Truncated Normal Model: mu=.5

  20. Effect of Differing Truncation Points From Coelli, Frontier4.1 (page 16)

  21. Other Models • Other Parametric Models (we will examine gamma later in the course) • Semiparametric and nonparametric – the recent outer reaches of the theoretical literature • Other variations including heterogeneity in the frontier function and in the distribution of inefficiency

  22. Test for Inefficiency? • Base test on u = 0 <=>  = 0 • Standard test procedures • Likelihood ratio • Wald • Lagrange Multiplier • Nonstandard testing situation: • Variance = 0 on the boundary of the parameter space • Standard chi squared distribution does not apply.

  23. Estimating ui • No direct estimate of ui • Data permit estimation of yi – β’xi. Can this be used? • εi = yi – β’xi= vi – ui • Indirect estimate of ui, using E[ui|vi – ui] • This is E[ui|yi,xi] • vi – ui is estimable with ei = yi – b’xi.

  24. Fundamental Tool - JLMS We can insert our maximum likelihood estimates of all parameters. Note: This estimates E[u|vi – ui], not ui.

  25. Other Distributions

  26. Technical Efficiency

  27. Application: Electricity Generation

  28. Estimated Translog Production Frontiers

  29. Inefficiency Estimates

  30. Estimated Inefficiency Distribution

  31. Estimated Efficiency

  32. Confidence Region Horrace, W. and Schmidt, P., Confidence Intervals for Efficiency Estimates, JPA, 1996.

  33. Application (Based on Costs)

  34. Sample Selection Modeling Switching Models: y*|technology = bt’x + v –u Firm chooses technology = 0 or 1 based on c’z+e e is correlated with v Sample Selection Model: Choice of organic or inorganic Adoption of some technological innovation

  35. Early Applications • Heshmati A. (1997), “Estimating Panel Models with Selectivity Bias: An Application to Swedish Agriculture”, International Review of Economics and Business 44(4), 893-924. • Heshmati, Kumbhakar and Hjalmarsson Estimating Technical Efficiency, Productivity Growth and Selectivity Bias Using Rotating Panel Data: An Application to Swedish Agriculture • Sanzidur Rahman Manchester WP, 2002: Resource use efficiency with self-selectivity: an application of a switching regression framework to stochastic frontier models:

  36. Sample Selection in Stochastic Frontier Estimation • Bradford et al. (ReStat, 2000):“... the patients in this sample were not randomly assigned to each treatment group. Statistically, this implies that the data are subject to sample selection bias. Therefore, we utilize astandard Heckman two-stage sample-selection process, creating an inverse Mill’s ratio from a first-stage probit estimator of the likelihood of CABG or PTCA. This correction variable is included in the frontier estimate....” • Sipiläinen and Oude Lansink (2005) “Possible selection bias between organic and conventional productioncan be taken into account [by] applying Heckman’s (1979) two step procedure.”

  37. Two Step Selection • Heckman’s method is for linear equations • Does not carry over to any nonlinear model • The formal estimation procedure based on maximum likelihood estimation • Terza (1998) – general results for exponential models with extensions to other nonlinear models • Greene (2006) – general template for nonlinear models • Greene (2010) – specific result for stochastic frontiers

  38. A Sample Selected SF Model di = 1[′zi + wi > 0], wi ~ N[0,12] yi = ′xi + i, i ~ N[0,2] (yi,xi) observed only when di = 1. i = vi- ui ui = |uUi| = u |Ui| where Ui ~ N[0,12] vi = vVi where Vi ~ N[0,12]. (wi,vi) ~ N2[(0,1), (1, v, v2)]

  39. Alternative Approach Kumbhakar, Sipilainen, Tsionas (JPA, 2008)

  40. Sample Selected SF Model

  41. Simulated Log Likelihood for a Stochastic Frontier Model The simulation is over the inefficiency term.

  42. 2nd Step of the MSL Approach

  43. JLMS Estimator of ui

  44. WHO Efficiency Estimates OECD Everyone Else

  45. WHO Estimates vs. SF Model