Non-Parametric Econometrics Emmanuel Flachaire
Emmanuel Flachaire
Non-Parametric Econometrics
Chapter 5
Semi-Parametric Regression Models
Emmanuel Flachaire
Non-Parametric Econometrics
Introduction I
A multiple regression model can be defined as: y = m(x1 , x2 , . . . , xk ) + ε
I
In theory: no problem. Ex: Nadaraya-Watson estimator can be used, with a multivariate kernel: Pn xk −xki x1 −x1i yi i=1 K h1 ; . . . ; hk m(x ˆ 1 , . . . , xk ) = P n xk −xki x1 −x1i i=1 K h1 ; . . . ; hk
I
In practice: the curse of dimensionality → m ˆ unreliable
I
Solution: semiparametric models
Emmanuel Flachaire
Non-Parametric Econometrics
Introduction Semiparametric models
I
Semiparametric models: mixing parametric and nonparametric specifications
I
Partial linear regression model: y = X β + m(z) + ε The relationship between y and X is parametric The relationship between y and z is nonparametric
I
Advantage: β with economic interpretation and robust to the specification at other parts of the model
I
It is a way to reduce the curse of dimensionality
Emmanuel Flachaire
Non-Parametric Econometrics
Introduction Semiparametric models
I
Dimension: 3 y = X β + m(z1 , z2 , z3 ) + ε
I
Dimension: 2 y = X β + m1 (z1 ) + m2 (z2 , z3 ) + ε
I
Dimension: 1 y = X β + m1 (z1 ) + m2 (z2 ) + m3 (z3 ) + ε
Emmanuel Flachaire
Non-Parametric Econometrics
Application Hedonic price
We consider the partial linear model: y = X β + m1 (z1 ) + m2 (z2 , z3 ) + ε I
y is the (log) price - 1135 observations, 1995 in Brest
I
X dummies: Studio, T1, T2, T3, T4, T5, house, parking
I
z1 : distance to the closest green park
I
z2 , z3 : geographical coordinates (location)
Spatial dependence is specified nonparametrically rather than with standard parametric models (spatial autocorrelation models)
Emmanuel Flachaire
Non-Parametric Econometrics
Application Hedonic price I
Results: X Const. T1 T2 T3 T4 T5 Maison Parking
I
coef 4.775 0.079 0.386 0.763 0.992 1.139 0.241 0.242
e.t. (0.052) (0.056) (0.051) (0.049) (0.050) (0.055) (0.032) (0.024)
With similar other characteristics: I I I
In average, a Studio costs 118.510 francs (e 4.775 ) a T2 is expected to cost 38.6% more than a Studio A house is expected to cost 21.1% more than an apartment Emmanuel Flachaire
Non-Parametric Econometrics
Application Green park influence
m ˆ 1 (z1 )
0.4 0.2 0.0 -0.2 -0.4 -0.6
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0
500 Emmanuel Flachaire
1000
1500
Non-Parametric Econometrics
Application Location influence
5.8
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.............................................................................................................................................................................................................................................................................. .. .. . . .. .. ... ... .. .. .. ..
102000
5.6
100000
5.4
z2
z1
98000
92000
94000
Emmanuel Flachaire
96000
98000
Non-Parametric Econometrics
Application Semiparametric to parametric model
I
Green park influence: nonparametric estimation suggests the following parametric model, m1 (z1 ) = γz1 + δ(z1 − 200)+
I
Location: nonparametric estimation suggests strong non-linearity, which is difficult to modelize parametrically: m2 (z2 , z3 ) =?
I
Finally, we consider the following semiparametric model: y = X β + γz1 + δ(z1 − 200)+ + m2 (z2 , z3 ) + ε
Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model I
In practice: arbitrage robustness vs. efficiency
I
Parametric model: efficiency, if the specification is correct
I
Nonparametric model: robustness to misspecification
I
The partial linear model is defined as: y = X β + m(Z ) + ε
I
Advantage 1: This model is robust to any form of the unknown function m √ Advantage 2: βˆ is n-consistent (Robinson 1988)
I
Finally, we have robustness + efficiency !!
I
Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Double residual estimator
I
The partial linear model is defined as y = X β + m(Z ) + ε
I
Apply a conditional expectation to both terms: E (y |Z ) = E (X |Z ) β + m(Z )
I
Substract both equations: y − E (y |Z ) = [X − E (X |Z )] β + ε
I
Conditional expectations known → linear regression model
Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Double residual estimator I
The partial linear regression model can be rewritten: y − E (y |Z ) = [X − E (X |Z )] β + ε
I
Conditional expectations unknown: use consistent estimators
I
E (y |Z ) and E (X |Z ): nonparametric estimators obtained from y = my (Z ) + ε1
I
X = mX (Z ) + ε2
Finally, the “double residual” estimator of β is the OLS estimator from the following model: y −m ˆ y = [X − m ˆX]β + ε εˆ1 = εˆ2 β + ε Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Double residual estimator
I
From the model: y −m ˆ y = [X − m ˆX]β + ε the OLS estimator, or double residual estimator, is βˆres = [(X − m ˆ x )> (X − m ˆ x )]−1 (X − m ˆ x )> (y − m ˆy)
I
From the model: εˆ1 = εˆ2 β + ε the OLS estimator, or double residual estimator is βˆres = (ˆ ε> ˆ2 )−1 εˆ> ˆ1 2ε 2ε
Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Double residual estimator I
The double residual estimator is asymptotically Normal βˆres = (ˆ ε> ˆ2 )−1 εˆ> ˆ1 2ε 2ε
I
Its variance is equal to σ2 V (βˆres ) = ε2 nσε2
I
Estimate of m(Z ) obtained by a nonparametric estimation of y − X βˆres = m(Z ) + ε.
I
Nonparametric estimation: local polynomial, splines, wavelets
I
Confidence interval and test Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Differencing I
Yatchew (1998): we can estimate β in the partial linear y = X β + m(z) + ε
I I
with one OLS estimation . . . no nonparametric estimation!! Sort the data (y , X , z) by z, such that z1 ≤ z2 ≤ · · · ≤ zn Differencing the model yields ys − ys−1 = (Xs − Xs−1 ) β + [m(zs ) − m(zs−1 )] + εs − εs−1
I
Approximately, we have: ys − ys−1 ≈ (Xs − Xs−1 ) β + εs − εs−1 because [m(zs ) − m(zs−1 )]→0 as n increases to ∞
I
OLS estimator of β from this model is consistent Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Differencing I
With sorted data, the partial linear model is approximately ∆y = ∆X β + η,
I
From which, a consistent estimator of β can be obtained βˆdiff = (∆X > ∆X )−1 ∆X > ∆y
I
This estimator is asymptotically Normal with variance σ2 V (βˆdiff ) = 1.5 ε2 nσε2
I
m(z) ˆ requires a nonparametric estimation y − X βˆdiff = m(z) + ε. Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Interpretation of coefficients
Parametric linear regression model I
FWL theorem - OLS βˆ are identical from the 2 models: y = Xβ + Zγ + ε
εˆ01 = εˆ02 β + ε0
whith εˆ01 and εˆ02 ≡ OLS residuals from y on Z and from X on Z I
Interpretation: βˆk ≡ net impact of variation of Xk over variation of y , net of the impact of any others variables Xj6=k
Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Interpretation of coefficients
Nonparametric regression model: double residual estimator I
βˆres identical from the 2 models: y = X β + m(Z ) + ε
εˆ1 = εˆ2 β + ε
where εˆ1 and εˆ2 ≡ NP residuals from y on Z and from X on Z I
Interpretation: βˆ ≡ similar to parametric regression
Emmanuel Flachaire
Non-Parametric Econometrics
Partial linear model Interpretation of coefficients
Nonparametric regression model: differencing I
Assume X and z not independent, such that X = g (z) + u
I
Differencing yields
ys −ys−1 = [g (zs )−g (zs−1 )] β+(us −us−1 ) β+[m(zs )−m(zs−1 )]+εs −εs−1 I
The two terms in brackets → 0 as the sample size increases
I
With n large enough, we have ys − ys−1 ≈ (us − us−1 ) β + εs − εs−1 βˆdiff ≈ βˆols : impact of u (part of X unexplained by z) over y
I
Interpretation: βˆ ≡ similar to parametric regression
Emmanuel Flachaire
Non-Parametric Econometrics
Additive model Definition
I
Nonparametric model y = m(Z1 , Z2 , . . . , Zk ) + ε
I
Additive model y = m1 (Z1 ) + m2 (Z2 ) + · · · + mk (Zk ) + ε
I
Additive separability: we assume m can be decompose as a sum of several functions of dimension one or two (or more)
I
Iterative estimation process
Emmanuel Flachaire
Non-Parametric Econometrics
Additive model Iterative estimation
I
Additive model: y = m1 (z1 ) + m2 (z2 ) + ε
I
Apply conditional expectations to both terms: E [y − m2 (z2 )|z1 ] = m1 (z1 ) E [y − m1 (z1 )|z2 ] = m2 (z2 )
I
With an estimate m ˆ 2 , regress y − m ˆ 2 on z1 −→ m ˆ1
I
With an estimate m ˆ 1 , regress y − m ˆ 1 on z2 −→ m ˆ2
Emmanuel Flachaire
Non-Parametric Econometrics
Additive model Iterative estimation
I
Additive model: y = m1 (z1 ) + m2 (z2 ) + ε
I
Iterative estimation 1. 2. 3. 4.
(0)
(0)
Select initial estimates m1 and m2 (i) (i−1) Obtain m ˆ 1 by regressing y − m ˆ2 on z1 (i) (i−1) Obtain m ˆ 2 by regressing y − m ˆ1 on z2 Repeat steps 2 an 3 until no significant changes
I
Initial estimates can be equal to 0 or obtained by OLS
I
Extension to more than 2 functions
Emmanuel Flachaire
Non-Parametric Econometrics
Additive model Additive separability
Additive separability hypothesis: what does it mean? I
we can decompose m as a sum of several functions
I
implications: a more restrictive function
I
what kind of restrictions ?
I
consequences ?
Emmanuel Flachaire
Non-Parametric Econometrics
Additive model Additive separability: m(z2 , z3 )
5.9
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5.8
5.7
5.6
5.5
5.4
5.3
92000
94000
Emmanuel Flachaire
96000
98000
Non-Parametric Econometrics
Additive model Additive separability: m2 (z2 ) + m3 (z3 )
6.0
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5.8
5.6
5.4
92000
94000
Emmanuel Flachaire
96000
98000
Non-Parametric Econometrics
Additive model Additive separability: z2 β2 + z3 β3
5.65
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5.60
5.55
5.50
92000
94000
Emmanuel Flachaire
96000
98000
Non-Parametric Econometrics
Heteroskedasticity Efficient estimator in parametric model
I
Linear regression model, with Ω = diag{σ12 , σ22 , . . . , σn2 }: y = Xβ + ε
V (ε|X ) = Ω
I
Consequences: OLS parameter consistent but not efficient
I
Efficient estimator: the GLS estimator is blue, βˆgls = (X > Ω−1 X )−1 X > Ω−1 y
V (βˆgls ) = (X > Ω−1 X )−1
I
A consistent estimate of Ω is required: σi2 = Wi γ
I
Feasible GLS: use σ ˆi , fitted values from εˆ2i = Wi γ + i
Emmanuel Flachaire
Non-Parametric Econometrics
Heteroskedasticity Efficient estimator in nonparametric model
I
The double residual estimator is given by an OLS estimation of y −m ˆ y = (X − m ˆx) β + ε
I
Nonparametric estimator m ˆ y and m ˆ x are still consistent
I
Efficient estimator: compute the FGLS estimator ˆ −1 (X − m ˆ −1 (y − m βˆgres = [(X − m ˆ x )> Ω ˆ x )]−1 (X − m ˆ x )> Ω ˆy) ˆ −1 (X − m V (βˆgres ) = [(X − m ˆ x )> Ω ˆ x )]−1 ,
I
Note that we can use a nonparametric model εˆ2i = g (Wi ) + i
Emmanuel Flachaire
Non-Parametric Econometrics
Heteroskedasticity Efficient estimator in nonparametric model
I
The differencing estimator is given by an OLS estimation of ∆y = ∆X β + η
I
It is a (parametric) linear regression model
I
With heteroskedasticity error terms, a GLS estimator is blue: βˆdiff = (∆X > Ω−1 ∆X )−1 ∆X > Ω−1 ∆y
I
In practice: replace Ω by a consistent estimator (FGLS)
Emmanuel Flachaire
Non-Parametric Econometrics
Heteroskedasticity Robust estimator in parametric model
I
Linear regression model, with Ω = diag{σ12 , σ22 , . . . , σn2 }: y = Xβ + ε
V (ε|X ) = Ω
I
Consequences: OLS parameter consistent, not OLS variance
I
Robust estimator: OLS parameter estimator with variance OK V (βˆols ) = (X > X )−1 (X > ΩX )−1 (X > X )−1
I I
ˆ = diag{ˆ Consistent estimate of X > ΩX : use Ω ε21 , εˆ22 , . . . , εˆ2n } ˆ is a consistent estimator of X > ΩX , but Ω ˆ Note that X > ΩX is not a consistent estimator of Ω
Emmanuel Flachaire
Non-Parametric Econometrics
Heteroskedasticity Robust estimator in nonparametric model
I
The double residual estimator is given by an OLS estimation of y −m ˆ y = (X − m ˆx) β + ε
I
Nonparametric estimator m ˆ y and m ˆ x are still consistent
I
Robust estimator: a consistent covariance matrix is given by
V (βˆres ) = [(X −m ˆ x )> (X −m ˆ x )]−1 (X −m ˆ x )> Ω (X −m ˆ x )[(X −m ˆ x )> (X −m ˆ x )]−1 I
ˆ = diag{ˆ Replace Ω by Ω ε21 , εˆ22 , . . . , εˆ2n }
I
Idem for the differencing estimator
Emmanuel Flachaire
Non-Parametric Econometrics
Autocorrelation Parametric model with autocorrelation I
AR(1) model: yt = Xt β + ε
εt = ρεt−1 + ηt
I
The covariance matrix of error terms V (ε|X ) is equal to 1 ρ ρ2 . . . ρn−1 1 ρ . . . ρn−2 ση2 ρ Ω= .. .. .. .. .. 2 1−ρ . . . . . n−1 n−2 n−3 ρ ρ ρ ... 1
I
Consequences: βˆols consistent but not efficient With consistent estimates of ση , ρ a consistent estimator of Ω can be obtained and used to get a GLS (efficient) estimator
I
βˆgls = (X > Ω−1 X )−1 X > Ω−1 y Emmanuel Flachaire
V (βˆgls ) = (X > Ω−1 X )−1
Non-Parametric Econometrics
Autocorrelation Nonparametric model with autocorrelation I
The double residual estimator is given by an OLS estimation of y −m ˆ y = (X − m ˆx) β + ε
I
Nonparametric estimator m ˆ y and m ˆ x are still consistent
I
Efficient estimator: compute the FGLS estimator ˆ −1 (X − m ˆ −1 (y − m βˆgres = [(X − m ˆ x )> Ω ˆ x )]−1 (X − m ˆ x )> Ω ˆy) ˆ −1 (X − m V (βˆgres ) = [(X − m ˆ x )> Ω ˆ x )]−1 ,
I
ˆ is a consistent estimator of Ω, based on σ Ω ˆη , ρˆ
I
Problem: m ˆ y and m ˆ x are consistent but kernel estimation may be poor because bandwidth selection is more problematic with autocorrelated error terms in nonparametic regression
I
Robust estimator (Newey-West): unreliable in finite sample Emmanuel Flachaire
Non-Parametric Econometrics
Autocorrelation Parametric dynamic model I
Partial autoregressive linear model: yt = β yt−1 + m(yt−2 ) + εt ,
I
The double residual estimator is the OLS estimator from yt − E (yt |yt−2 ) = β [yt−1 − E (yt−1 |yt−2 )] + εt if we replace the expectations by consistent estimates
I
The double residual estimator is asymptotically Normal
I
Its variance is σε2 /(nσε22 ), with σε22 ← regress yt−1 on yt−2
I
We can use other models, as the additive model: yt = m1 (yt−1 ) + m2 (yt−2 ) + εt
Emmanuel Flachaire
Non-Parametric Econometrics
Endogeneity Parametric linear model
I
The linear regression model is defined as, y = Xβ + ε
I
If E (ε|X ) 6= 0, OLS estimation is not valid, we should use IV
I
Use instruments W , correlated to X , not to ε
I
IV estimation: regress y on PW X by OLS βˆiv = (X > PW X )−1 X > PW y
I
V (βˆiv ) = σ 2 (X > PW X )−1 ,
PW X is the part of X explained by W : OLS fitted values from X = Wπ + ν
Emmanuel Flachaire
Non-Parametric Econometrics
Endogeneity Partial linear model
I
The partial linear regression model is defined as, y = X β + m(Z ) + ε
I
Correlation between ε et regressors can be: I
with X : in the parametric part of the model
I
with Z : in the nonparametric part of the model
Emmanuel Flachaire
Non-Parametric Econometrics
Endogeneity in the parametric part of the partial linear model I
The partial linear regression model is defined as, y = X β + m(Z ) + ε
I
E (ε|X ) 6= 0 E (ε|Z ) = 0
The double residual estimator is given by an OLS estimation of y −m ˆ y = (X − m ˆx) β + ε
I
Nonparametric estimator m ˆ y and m ˆ x are still consistent, since Z is not endogeneous
I
We can compute IV estimator from the model above: βˆvires = [(X − m ˆ x )> PW (X − m ˆ x )]−1 (X − m ˆ x )> PW (y − m ˆ y ). V (βˆivres ) = σε2 [(X − m ˆ x )> PW (X − m ˆ x )]−1 Emmanuel Flachaire
Non-Parametric Econometrics
Endogeneity in the nonparametric part of the partial linear model
I
The partial linear regression model is defined as, y = X β + m(Z ) + ε
I
E (ε|X ) = 0
E (ε|Z ) 6= 0
The double residual estimator is given by an OLS estimation of y −m ˆ y = (X − m ˆx) β + ε
I
Nonparametric estimator m ˆ y and m ˆ x are not consistent, since Z is endogeneous
I
We cannot compute IV estimator from the model above!
Emmanuel Flachaire
Non-Parametric Econometrics
Endogeneity IV estimation
I
The partial linear regression model is defined as, y = X β + m(Z ) + ε
I
E (ε|X ) = 0
E (ε|Z ) 6= 0
If we apply the double residual principle, we obtain E (y |W ) = E (X |W )β + E [m(Z )|W ].
I
The nonparametric term does not disappear!
I
Solution: ill-posed problem → difficult to solve
Emmanuel Flachaire
Non-Parametric Econometrics
Endogeneity Control function I
Assume that W is correlated to Z , not to ε, such that Z = Wπ + ν
E (ν|W ) = 0
I
Additional hypothesis: E (ε|Z , ν) = ρν
I
Thus we have ε = ρν + η, the partial linear model becomes y = X β + m(Z ) + νρ + η with η uncorrelated to regressors
I
If we apply the double residual principle, we obtain y − E (y |Z ) = [X − E (X |Z )]β + [ν − E (ν|Z )]ρ + η.
I
Replace ν by OLS residuals from the first model above
I
Note that an exogeneous test can be done with H0 : ρ = 0 Emmanuel Flachaire
Non-Parametric Econometrics
Discrete choice model Parametric model I
A binary discrete choice model is defined as y◦ = Xβ + ε
ε ∼ F (0, 1),
I
We do not observe y ◦ but a binary variable y
I
The expectation of y with respect to X is defined as E (y |X ) = P(y = 1|X ) = F (X β).
I
That is, y ∼ Bernouilli with parameter P(y = 1|X ) = F (X β)
I
Maximum likelihood estimation (ML) `(y , β) =
n X
yt log F (Xt β) + (1 − yt ) log 1 − F (Xt β)
t=1 I
F is a distribution chosen a priori - Logistic or Normal Emmanuel Flachaire
Non-Parametric Econometrics
Discrete choice model Partial linear model I
The partial linear model is defined as E (y |X , Z ) = F [X β + m(Z )]
I
Iterative estimation: with m ˆ (i) we estimate β by ML `(y , β) =
n X
yt log F [Xt β+m ˆ (i) ]+(1−yt ) log 1−F [Xt β+m ˆ (i) ]
t=1 I
With βˆ(i) , we can estimate m by ML
`(y , m) =
n X
yt log F [Xt βˆ(i) +m(Z )]+(1−yt ) log 1−F [Xt βˆ(i) +m(Z )]
t=1 I
Maximization requires to solve nonlinear optimisation problem Emmanuel Flachaire
Non-Parametric Econometrics
Discrete choice model Index model
I
If F is misspecified, ML estimator is inconsistent!
I
The index model is defined as E (y |X ) = F (X β),
I
where F is an unknown function estimated nonparametrically ˆ we can estimate F from the nonparametric model With β, ˆ +η y = F (X β)
I
Estimation of β is not easy
Emmanuel Flachaire
Non-Parametric Econometrics