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The 1 CES production function The homogenous Constant Elasticity of Substitution (CES) production function takes the form Q = K + (1 )L n o 1/ exp(U), 1, 0 1, > 0, (1) where K is capital, L is labor, Q is output, and U is an error term satisfying E[U |K, L] = 0. The CES production function was introduced by Arrow, Chenery, Minhas and Solow1 in 1961 Formally, the elasticity of substitution measures the percentage change in factor proportions due to a percentage change in the marginal rate of technical substitution. In particular, for a canonical production function Q = f(K, L) with marginal products fK = f (K, L)/ K and fL = f (K, L)/ L, the marginal rate of technical substitution is fL /fK , i.e., minus the slope of the isoquant in point (L, K), hence the elasticity of substitution between capital and labor is given by: = d ln(L/K)/d ln(fL /fK ). In the case of the deterministic homogenous CES production function Q = { K + (1 )L } 1/ we have fL = K + (1 )L fK = K + (1 )L n n o (1+ )/ o (1+ )/ (1 )L 1 , K 1 , hence d ln (fL /fK ) = ( + 1)d ln (L/K) and thus = 1/( + 1). In order to estimate the parameters of the CES production function via EasyReg, rewrite (1) as ln(Q/L) = ln( ) 1 ln { [exp ( ln(L/K)) 1] + 1} + U ln { [exp ( ln(L/K)) 1] + 1} = ln( ) [exp ( ln(L/K)) 1] exp ( ln(L/K)) 1 ( ln(L/K)) + U. ln(L/K) (2) Arrow, K.J., H.B. Chenery, B.S. Minhas and R.M. Solow (1961), Capital-Labor Substitution and Economic E ciency , Review of Economics and Statistic. 1 1 It is an elementary calculus exercise to verify that lim ln { [exp ( ln(L/K)) 1] + 1} ln(1 + ) ln(1) = lim 0 [exp ( ln(L/K)) 1] d ln(x) = = 1, dx x=1 0 hence it follows that for 0 (2) becomes ln(Q/L) = ln( ) ln(L/K) + U. Thus, for = 0 the CES production function becomes a Cobb-Douglas production function: ln(Q) = ln( ) + ln(K) + (1 ) ln(L) + U. Y = g(x, b) + U, where Y = ln(Q/L), x = ln(L/K), b = (b(1), b(2), b(3))0 = (ln( ), , )0 , and g(x, b) = b(1) ln {b(3) [exp (b(2)x) 1] + 1} b(3) [exp (b(2)x) 1] exp (b(2)x) 1 (b(3)x) . b(2)x (4) (3) exp ( ln(L/K)) 1 exp( ) exp(0) d exp(x) lim = lim = = 1, 0 0 ln(L/K) dx x=0 The CES production function (2) is now a nonlinear regression model, 2 2.1 Specifying the CES production function in EasyReg Selection of the initial X variables In EasyReg a nonlinear regression function is build up recursively by augmenting the list of X variables with nonlinear transformations and linear and/or multiplicative combinations previous of X variables. In order to build up (4), we have to select two initial X variables, X(1) = ln(L/K) and X(2) = 1. The latter is necessary for two reasons: First, EasyReg does not allow to specify constants directly. Second the parameters b(2) and b(3) are common to di erent transformations. The constant X(2) = 1 enables us to associate them to new X variables. 2 2.2 Storing the parameters in X variables Thus, we need to specify three new X variables rst, each associated with a parameter, by selecting X(2) and choosing the Linear combination option three times: X(3) = b(1)X(2), X(4) = b(2)X(2), X(5) = b(3)X(2). Then (4) becomes: g(x, b) = X(3) ln {X(5) [exp (X(1)X(4)) X(2)] + 1} X(5) [exp (X(1)X(4)) X(2)] exp (X(1)X(4)) 1 X(1)X(5), X(1)X(4) Now the CES production function involved is build up recursively as follows. X(.) X(1) X(2) X(3) X(4) X(5) X(6) X(7) X(8) X(9) X(10) = = = = = = = = = = Transformation ln(L/K) 1 b(1)X(2) = b(1) b(2)X(2) = b(2) b(3)X(2) = b(3) X(1)X(4) exp(X6)) X(7) X(2) X(5)X(8) ln (X(9) + 1) /X(9) Actual transformation Transformation option ln( ) ln(L/K) exp ( ln(L/K)) exp ( ln(L/K)) 1 (exp ( ln(L/K)) 1) ln( (exp( ln(L/K)) 1)+1) (exp( ln(L/K)) 1) exp( ln(L/K)) 1 ln(L/K) Linear combination Linear combination Linear combination Multiply EXP(z) [z = X(6)] Subtract Multiply LOG(z+1)/z [z = X(9)] (EXP(z)-1)/z [z = X(6)] Multiply X(11) = (exp (X(6)) 1) /X(6) X(12) = X(1)X(5)X(10)X(11) X(13) = X(3) X(12) ln(L/K) ln( (exp( ln(L/K)) 1)+1) (exp( ln(L/K)) 1) exp( ln(L/K)) 1 ln(L/K) ln( ) ln(L/K) ln( (exp( ln(L/K)) 1)+1) (exp( ln(L/K)) 1) ln(L/K)) 1 exp( ln(L/K) = g(b, x) Subtract As you see, this is actually a simple computer program, like a macro in MS Word or Corel Wordperfect. 3 2.3 The non-homogenous CES production function n o / The general CES production function takes the form exp(U), 1, 0 1, > 0, > 0, (5) where is the degree of homogeneity: if K and L are both increased with a factor , then Q increases with a factor . Thus, if > 1 we have increasing return to scale, and if < 1 we have decreasing returns to scale. In this case (2) becomes ln(Q/L) = ln( ) ln { [exp ( ln(L/K)) 1] + 1} + U ln { [exp ( ln(L/K)) 1] + 1} = ln( ) [exp ( ln(L/K)) 1] exp ( ln(L/K)) 1 ( ln(L/K)) + U. ln(L/K) (6) Q = K + (1 )L The speci cation of (6) in EasyReg is the same as steps X(1) through X(12), with X(13) replaced with the following three steps: X Transformation X(13) = b(4)X(2) = b(4) (= ) X(14) = X(12)X(13) X(15) = X(3) X(14) Transformation option Linear combination Multiply Subtract 4
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Penn State >> ECON >> 501 (Fall, 2008)
Orthonormal Polynomials, Related Orthonormal Functions and the Hilbert Spaces they Span Herman J. Bierens December 5, 2008 1 Orthogonal Polynomials Let w(x) be a non-negative Borel measurable real-valued function on R satisfying Z |x|k w(x)dx (0,...
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The Econometric Consequences of the Ceteris Paribus Condition in Economic Theory Herman J. Bierens Pennsylvania State University, USA & Tilburg University, the Netherlands Norman R. Swanson Pennsylvania State University, USA September 1998 Abstract ...
Penn State >> ECON >> 501 (Fall, 2008)
Introduction to the Mathematical and Statistical Foundations of Econometrics Remaining corrections and improvements in the 2004 and 2007 editions1 December 12, 2008 Page 8, section 1.2.3: Some of my students had difficulties understanding the deri...
Penn State >> ECON >> 501 (Fall, 2008)
A Competing Risk Analysis of Recidivism Jos R. Carvalho Federal University of Ceara, Brazil Herman J. Bierens Pennsylvania State University, USA & Tilburg University, The Netherlands November 3, 2002 Abstract In this paper we build and estimate an ...
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Sample Moments Integrating Normal Kernel (SMINK) density and regression estimators 1 SMINK density estimation Let X1; :; Xn be a random sample from a k-variate absolutely continuous distribution with density f (x); expectation ; and non-singular vari...
Penn State >> ECON >> 501 (Fall, 2008)
! \" % \" \" \" 0 \" \" # # ./ $ %1 % % + , # \" . < # \" \" ( 5. 7# 89 / \" 1 \" / , 8 # 1 3 2 : \';. 6 9 \". 9\" 4* \" 3# * 8 4 \"> 8. >\" - : . %9*= ,- 2\" \'+) 4 B 9 - * 4 -4 ? 28 )\'@ )+; @!< 3 8 )\'@ )+< @( \'...
Penn State >> ECON >> 501 (Fall, 2008)
Forecasting Quarterly Brazilian GDP Growth Rate With Linear and NonLinear Diusion Index Models Roberto Tatiwa Ferreiraa, Herman Bierensb, Ivan Castelarc a,c Universidade b Pennsylvania Federal do Cear (CAEN/UFC), Brazil a State University, U. S. A. ...
Penn State >> ECON >> 501 (Fall, 2008)
Time Varying Cointegration Herman J. Bierens and Luis F. Martins May 3, 2008 Abstract In this paper we propose a time varying cointegration vector error correction model in which the cointegrating relationship varies smoothly over time. The Johansen...
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Integrated Conditional Moment Tests for Parametric Conditional Distributions Herman J. Bierens and Li Wang Pennsylvania State University Department of Economics University Park, PA 16802 This paper extends the Integrated Conditional Moment (ICM) test...
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REVIEW OF CALCULUS Herman J. Bierens Pennsylvania State University (January 28, 2004) 1. Summation Let x1 , x2 , . , xn be a sequence of numbers. The sum of these numbers is usually denoted by x1 % x2 %.% xn \' j xj , or x1 % x2 %.% xn \' \'j\'1xj . n ...
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...
Penn State >> ECON >> 501 (Fall, 2008)
...
Penn State >> ECON >> 501 (Fall, 2008)
Conditional Treatment and Its Eect on Recidivism* Jos R. Carvalho* e Herman J. Bierens* Abstract The objective of this paper is to evaluate the eect of the 1985 Employment Services for Ex-Oenders (ESEO) program on recidivism. Initially, the sample ha...
Penn State >> ECON >> 501 (Fall, 2008)
Job Search, Conditional Treatment and Recidivism: The Employment Services for Ex-Oenders Program Reconsidered Herman J. Bierens Department of Economics, Pennsylvania State University Jos R. Carvalho CAEN, Universidade Federal do Cear, Brazil. June 12...
Penn State >> ECON >> 501 (Fall, 2008)
Separate Appendix to: Nonparametric Nonlinear Co-Trending Analysis, With an Application to Interest and Inflation in the U.S. Herman J. Bierens Pennsylvania State University, Department of Economics, University Park, PA 16802 & Tilburg University, t...
Penn State >> ECON >> 501 (Fall, 2008)
Semi-Nonparametric Identication of the Right Censored Mixed Proportional Hazard Model Herman J. Bierens Department of Economics Pennsylvania State University November 3, 2008 Abstract Elbers and Ridder (1982) and Heckman and Singer (1984) have shown ...
Penn State >> ECON >> 501 (Fall, 2008)
Journal of Econometrics 108 (2002) 343 363 www.elsevier.com/locate/econbase Nonparametric tests for unit roots and cointegration Jorg Breitung Institute of Statistics and Econometrics, Humboldt University Berlin, Spandauer Strasse 1, D-10178 Berl...
Penn State >> ECON >> 501 (Fall, 2008)
Weak Convergence to the Matrix Stochastic R1 Integral 0 BdB 0 in the Gaussian Case, with Application to Likelihood-Based Cointegration Analysis Herman J. Bierens Pennsylvania State University March 3, 2007 Abstract Phillips (1988) has set forth condi...
Penn State >> ECON >> 501 (Fall, 2008)
THE CLASSICAL LINEAR REGRESSION MODEL Herman J. Bierens Pennsylvania State University September 1, 2002 1. Introduction The classical linear regression model takes the form y j \' 21 x 1,j % . % 2kx k,j % uj , j \' 1,.,n , unobservable error terms, n i...
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Integrated Conditional Moment Testing of Median Regression Models Herman J. Bierens1 Pennsylvania State University, U.S.A. Tilburg University, The Netherlands Donna K. Ginther Washington University, St. Louis, U.S.A. Current version: March 23, 200...
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Testing the unit root with drift hypothesis against nonlinear trend stationarity, with an application to the U.S. price level and interest rate 1 Herman J.Bierens 2 Pennsylvania State University, USA, and Tilburg University, the Netherlands (Novemb...
Penn State >> ECON >> 501 (Fall, 2008)
Separate Appendix to: Time Varying Cointegration Herman J. Bierens and Luis F. Martins May 2, 2008 Abstract In this separate appendix to Bierens and Martins (2008), Time Varying Cointegration, the proof of Theorem 2 is given and the results for the d...
Penn State >> ECON >> 501 (Fall, 2008)
AO, 5WBNw+WAv 6 AO, ,66WW,v N# 6 AO, Wj,# +AWw O~+# #,w + Djji| -aaji BAa Cj6jA bN|jitjA_ N?iht|) Lu 5L|ih? @*uLh?@ @?_ N?iht|) Lu `it|ih? ?|@hL Li4Mih Sc 2ff lj+NiatH Gxudwlrq/ Vhpl0sdudphwulf Hflhqf| Erxqg/ Pl{hg Sursruwlrqdo Kd}dug1 W?|hL_U|L?...
Penn State >> ECON >> 501 (Fall, 2008)
Separate Appendix to: Econometric Analysis of Linearized Singular Dynamic Stochastic General Equilibrium Models Herman J. Bierens Pennsylvania State University and Tilburg University Derivation of (18): 1X ln [pt1 (, , 1 , Q, 1 | )] n t=1 n = (t1...
Penn State >> ECON >> 501 (Fall, 2008)
Econometric Analysis of Linearized Singular Dynamic Stochastic General Equilibrium Models Herman J. Bierens Pennsylvania State University Abstract In this paper I propose an alternative to calibration of linearized singular dynamic stochastic genera...
Penn State >> ECON >> 501 (Fall, 2008)
Nonparametric Cointegration Analysis Herman J. Bierens1 Pennsylvania State University, U.S.A., and Tilburg University, the Netherlands In this paper we propose consistent cointegration tests, and estimators of a basis of the space of cointegrating ve...
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Testing the regional restructuring hypothesis in western Germany Herman J. Bierens Department of Economics, Pennsylvania State University, 608 Kern Graduate Building, University Park, PA 16802, USA; e-mail: hbierens@psu.edu Thomas Kontuly Department ...
Penn State >> ECON >> 501 (Fall, 2008)
Review of the Integrated Conditional Moment Test and Its Implementation in EasyReg International Herman J. Bierens Pennsylvania State University April 21, 2006 1 The ICM test The ICM test is based on the following theorem: THEOREM 1: Let u be a ra...
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Integrated Conditional Moment Tests for Parametric Conditional Distributions of Stationary Time Series Processes Herman J. Bierens and Li Wang Department of Economics and CAPCP Pennsylvania State University University Park, PA 16802 April 29, 2008 A...
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The Logit Model: Estimation, Testing and Interpretation Herman J. Bierens October 25, 2008 1 1.1 Introduction to maximum likelihood estimation The likelihood function Consider a random sample Y1 , ., Yn from the Bernoulli distribution: Pr[Yj = 1] ...
Penn State >> ECON >> 501 (Fall, 2008)
The Right-Censored Proportional Hazard Model and its Implementation in EasyReg Herman J. Bierens May 10, 2005 1 1.1 The right-censored mixed proportional hazard model The proportional hazard model Let T be a duration, and let X be a vector of cova...
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An Econometric Model of Credit Spreads with Rebalancing, ARCH and Jump Eects1 Herman Bierens2 Economics Department, Penn State University Jing-zhi Huang3 Smeal College, Penn State University and Stern School, NYU Weipeng Kong4 Smeal College of Busine...
Penn State >> ECON >> 501 (Fall, 2008)
...
Penn State >> ECON >> 501 (Fall, 2008)
The Sample Moments Integrating Normal Kernel (SMINK) density estimator Let X1 , ., Xn be a random sample from a k-variate absolutely continuous distribution with density f(x), expectation , and non-singular variance matrix . Let x(i) be the i-th comp...
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Urban Studies (1985) 22, 83-90 1985 Urban Studies Notes and Comments Population Forecasting at the City Level: An Econometric Approach Herman J. Bierens and Roy Hoever 1. Introduction tFirst received, April 1983; in final form, December 1983] The...
Penn State >> ECON >> 501 (Fall, 2008)
Semi-Nonparametric Estimation of First-Price Auctions Models with Auction-Specic Heterogeneity via an Integrated Simulated Conditional Moments Method Herman J. Bierensa and Hosin Songb a Department of Economics and CAPCP Pennsylvania State Universit...
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The Interval-Censored Semi-Nonparametric Mixed Proportional Hazard Model and its Implementation in EasyReg Herman J. Bierens May 10, 2005 1 The mixed proportional hazard model This EasyReg module (SNPSURVIVAL) estimates a semi-nonparametric (SNP) ...
Penn State >> ECON >> 501 (Fall, 2008)
Introduction to the Mathematical and Statistical Foundations of Econometrics Errata to the first edition April 5, 2007 Page 10, line 2 from bottom: Page 10, line 1 from bottom: Page 20, line 5 from bottom: Page 37, line 2 of Section 2.1: Page 37, lin...
Penn State >> ECON >> 501 (Fall, 2008)
-2- INTRODUCnON Artificial neural networks are a class of models developed by cognitive scientists interested in understanding how computation is performed by the brain. These networks are capable of learning through a process of trial and error th...
Penn State >> ECON >> 501 (Fall, 2008)
Comparison of Probit and Logit Analysis The following gure compares the standard normal density f(x) with the density g(x) of the rescaled Logit distribution G(x) = i.e., 1 , 1 + exp (x/) 1 G(x) (1 G(x) , where is chosen such that G(1.96) = 0.975...
Penn State >> ECON >> 501 (Fall, 2008)
...
Penn State >> ECON >> 501 (Fall, 2008)
Breitungs nonparametric unit root tests 1. 1.1 The Breitung tests The unit root hypothesis versus zero-mean stationarity Consider the null hypothesis that the time series Y t , t = 1, .,n, is a unit root process: H0: Y t \' Yt&1 % Ut , (1) which yo...
Penn State >> ECON >> 501 (Fall, 2008)
ECON 511: Time series econometrics Theoretical Homework 1 1. Let Xt be a zero-mean covariance stationary process for which the linear projection of Xt Xt \' Xtm] \' 0 for m \' 1,2,3,. 4 4 on {Xt1,...
Penn State >> ECON >> 501 (Fall, 2008)
ECON 511: Time series econometrics Theoretical homework 2 A time series Xt, t < 4, is always assumed to be defined on a common probability 1. space {,P}. Suppose that Xt is generated by tossing a fair coin at each time t: Xt = 1 if the outcom...
Penn State >> ECON >> 501 (Fall, 2008)
Let {Xj } be a sequence of random variables j=1 satisfying E[Xj ] = 0, E[|Xi.Xj |] 2|ij|, E[Xj2] = 1 Prove that n 1X Xj = 0. plim n j=1 n 1 ...
Penn State >> ECON >> 501 (Fall, 2008)
THE PENNSYLVANIA STATE UNIVERSITY DEPARTMENT OF ECONOMICS SPRING 1997 ECON 501 Introduction to Statistics and Econometrics 167 Willard TR 9:45-11:00 AM Prof. Herman J. Bierens Office: 615 Kern (Temporary) Office Hours: To Be Announced in Class Office...
Penn State >> ECON >> 501 (Fall, 2008)
Complex Unit Roots and Business Cycles: Are They Real? Herman J. Bierensy Pennsylvania State University, and Tilburg University Abstract In this paper the asymptotic properties of ARMA processes with complex-conjugate unit roots in the AR lag polyno...
Penn State >> ECON >> 501 (Fall, 2008)
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Penn State >> ECON >> 501 (Fall, 2008)
SPECIFICATION OF ECONOMETRIC MODELS Herman J. Bierens Pennsylvania State University April 11, 2004 1 Functional form Most econometric models link an observable dependent variable Y to observable explanatory variables X1,.,Xm, an unobservable varia...
Penn State >> ECON >> 501 (Fall, 2008)
ECON 511: Time series econometrics Theoretical homework 3 1. Consider the strictly stationary zero-mean ARMA(1,1) process Y t : Y t \' 0Yt 0Ut 1, |0| < 1, 0 0, 0 0, 0 0, Ut - i.i.d. N 0,0 . 2 (1) You may assume that Y t has a...
Penn State >> ECON >> 501 (Fall, 2008)
Introduction to EasyReg International Herman J. Bierens Pennsylvania State University April 15, 2007 1. Introduction EasyReg (Easy Regression) International is a free econometrics software package, which can be downloaded from URL http:/econ.la.ps...
Penn State >> ECON >> 501 (Fall, 2008)
Table 4: Corrected quantiles of the T-Tilde test: p \' P(T # T) p 0.010 0.025 0.050 0.100 0.250 0.500 0.750 0.900 0.950 0.975 0.990 m 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 0.01 1.07 6.08 21.56 39.11 73.70 110.93 157.62 218.67 310.71 382.70 505.88...
Penn State >> ECON >> 501 (Fall, 2008)
UNIT ROOTS Herman J. Bierens1 Pennsylvania State University (October 30, 2007) 1. Introduction In this chapter I will explain the two most frequently applied types of unit root tests, namely the Augmented Dickey-Fuller tests [see Fuller (1996), Di...
Penn State >> ECON >> 501 (Fall, 2008)
The Uniform Weak Law of Large Numbers and the Consistency of M-Estimators of Cross-Section and Time Series Models Herman J. Bierens Pennsylvania State University September 16, 2005 1. The uniform weak law of large numbers In econometrics we often h...
Penn State >> ECON >> 501 (Fall, 2008)
SEMI-NONPARAMETRIC INTERVAL-CENSORED MIXED PROPORTIONAL HAZARD MODELS: IDENTIFICATION AND CONSISTENCY RESULTS Herman J. Bierens Pennsylvania State University January 14, 2008 Abstract In this paper I propose to estimate distributions on the unit int...
Penn State >> ECON >> 501 (Fall, 2008)
FORECASTING Herman J. Bierens Pennsylvania State University November 2008 1. Recursive best linear forecasting Let Y t be a covariance stationary time series process, with E[Y t] \' 0 . The best linear h- step ahead forecast of Yt%h , h \' 1,2,3,., ...
Penn State >> ECON >> 511 (Fall, 2008)
ECON 511: Time series econometrics Theoretical homework assignment 4 Consider the bivariate VAR(1) process xt yt where A\' 0.5 0 , and ut vt - i.i.d. N2 0 0 , . \'A xt1 % ut vt , &0.2 0.7 (a) What is the condition for stationarity of the proc...
Penn State >> ECON >> 511 (Fall, 2008)
Semi-Nonparametric Estimation of Independently and Identically Repeated First-Price Auctions via an Integrated Simulated Moments Method Herman J. Bierens Pennsylvania State University Hosin Song Korea Institute of Public Finance December 19, 2008 1 ...
Penn State >> ECON >> 511 (Fall, 2008)
How to estimate a static or dynamic linear regression model if the time series involved have missing values in between valid values Herman J. Bierens Pennsylvania State University December 11, 2006 1 Introduction In principle EasyReg only allows m...
Penn State >> ECON >> 511 (Fall, 2008)
Let {Xj }n be random sample from the norj=1 mal distribution with unknown expectation 0 and unknown variance 2. However, it is known that 0 is contained in the interval = [10, 10]. An alternative to using the sample mean as an estimator of 0 is to ...
Penn State >> ECON >> 511 (Fall, 2008)
Separate Appendix to: NONPARAMETRIC COINTEGRATION ANALYSIS by Herman J.Bierens Pennsylvania State University, and Tilburg University, The Netherlands Following Phillips (1987), we use throughout this appendix the symbol \"Y\" to indicate weak converg...
Penn State >> ECON >> 511 (Fall, 2008)
Introduction to the Mathematical and Statistical Foundations of Econometrics Errata to the first edition April 5, 2007 Page 10, line 2 from bottom: Page 10, line 1 from bottom: Page 20, line 5 from bottom: Page 37, line 2 of Section 2.1: Page 37, lin...
Penn State >> ECON >> 511 (Fall, 2008)
Comparison of Probit and Logit Analysis The following gure compares the standard normal density f(x) with the density g(x) of the rescaled Logit distribution G(x) = i.e., 1 , 1 + exp (x/) 1 G(x) (1 G(x) , where is chosen such that G(1.96) = 0.975...
Penn State >> ECON >> 511 (Fall, 2008)
1 The CES production function The homogenous Constant Elasticity of Substitution (CES) production function takes the form Q = K + (1 )L n o1/ exp(U), 1, 0 1, > 0, (1) where K is capital, L is labor, Q is output, and U is an error term sa...
Penn State >> ECON >> 511 (Fall, 2008)
Semi-nonparametric estimation of independently and identically repeated rst-price auctions via an integrated simulated moments method Herman J. Bierensa and Hosin Songb a Department of Economics and CAPCP Pennsylvania State University, University Par...
Penn State >> ECON >> 511 (Fall, 2008)
Orthonormal Polynomials, Related Orthonormal Functions and the Hilbert Spaces they Span Herman J. Bierens December 5, 2008 1 Orthogonal Polynomials Let w(x) be a non-negative Borel measurable real-valued function on R satisfying Z |x|k w(x)dx (0,...
Penn State >> ECON >> 511 (Fall, 2008)
Introduction to Hilbert Spaces Herman J. Bierens Pennsylvania State University (June 24, 2007) 1. Vector spaces The notion of a vector space should be known from linear algebra: Definition 1. Let V be a set endowed with two operations, the operat...
Penn State >> ECON >> 511 (Fall, 2008)
The Tobit model Herman J. Bierens September 17, 2004 1 The model The Tobit1 model assumes that the observed dependent variables Yj for observations j = 1; :; n satisfy Yj = max Yj; 0 ; (1) where the Yjs are latent variables generated by the cla...
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