Heteroskedasticity-consistent standard errors

Heteroskedasticity-consistent standard errors are introduced by Friedhelm Eicker,[6][7] and popularized in econometrics by Halbert White.

Consider the linear regression model for the scalar ${\displaystyle y}$.

${\displaystyle y=\mathbf {x} ^{\top }{\boldsymbol {\beta }}+\varepsilon ,\,}$

where ${\displaystyle \mathbf {x} }$ is a k x 1 column vector of explanatory variables (features), ${\displaystyle {\boldsymbol {\beta }}}$ is a k × 1 column vector of parameters to be estimated, and ${\displaystyle \varepsilon }$ is the residual error.

The ordinary least squares (OLS) estimator is

${\displaystyle {\widehat {\boldsymbol {\beta }}}_{\mathrm {OLS} }=(\mathbf {X} ^{\top }\mathbf {X} )^{-1}\mathbf {X} ^{\top }\mathbf {y} .\,}$

where ${\displaystyle \mathbf {y} }$ is a vector of observations ${\displaystyle y_{i}}$, and ${\displaystyle \mathbf {X} }$ denotes the matrix of stacked ${\displaystyle \mathbf {x} _{i}}$ values observed in the data.

If the sample errors have equal variance ${\displaystyle \sigma ^{2}}$ and are uncorrelated, then the least-squares estimate of ${\displaystyle {\boldsymbol {\beta }}}$ is BLUE (best linear unbiased estimator), and its variance is estimated with

${\displaystyle {\hat {\mathbb {V} }}\left[{\widehat {\boldsymbol {\beta }}}_{\mathrm {OLS} }\right]=s^{2}(\mathbf {X} ^{\top }\mathbf {X} )^{-1},\quad s^{2}={\frac {\sum _{i}{\widehat {\varepsilon }}_{i}^{2}}{n-k}}}$

where ${\displaystyle {\widehat {\varepsilon }}_{i}=y_{i}-\mathbf {x} _{i}^{\top }{\widehat {\boldsymbol {\beta }}}_{\mathrm {OLS} }}$ are the regression residuals.

When the error terms do not have constant variance (i.e., the assumption of ${\displaystyle \mathbb {E} [\mathbf {u} \mathbf {u} ^{\top }]=\sigma ^{2}\mathbf {I} _{n}}$ is untrue), the OLS estimator loses its desirable properties. The formula for variance now cannot be simplified:

${\displaystyle \mathbb {V} \left[{\widehat {\boldsymbol {\beta }}}_{\mathrm {OLS} }\right]=\mathbb {V} {\big [}(\mathbf {X} ^{\top }\mathbf {X} )^{-1}\mathbf {X} ^{\top }\mathbf {y} {\big ]}=(\mathbf {X} ^{\top }\mathbf {X} )^{-1}\mathbf {X} ^{\top }\mathbf {\Sigma } \mathbf {X} (\mathbf {X} ^{\top }\mathbf {X} )^{-1}}$

where ${\displaystyle \mathbf {\Sigma } =\mathbb {V} [\mathbf {u} ].}$

While the OLS point estimator remains unbiased, it is not "best" in the sense of having minimum mean square error, and the OLS variance estimator ${\displaystyle {\hat {\mathbb {V} }}\left[{\widehat {\boldsymbol {\beta }}}_{\mathrm {OLS} }\right]}$ does not provide a consistent estimate of the variance of the OLS estimates.

For any non-linear model (for instance logit and probit models), however, heteroskedasticity has more severe consequences: the maximum likelihood estimates of the parameters will be biased (in an unknown direction), as well as inconsistent (unless the likelihood function is modified to correctly take into account the precise form of heteroskedasticity).[8][9] As pointed out by Greene, “simply computing a robust covariance matrix for an otherwise inconsistent estimator does not give it redemption.”[10]

If the regression errors ${\displaystyle \varepsilon _{i}}$ are independent, but have distinct variances ${\displaystyle \sigma _{i}^{2}}$, then ${\displaystyle \mathbf {\Sigma } =\operatorname {diag} (\sigma _{1}^{2},\ldots ,\sigma _{n}^{2})}$ which can be estimated with ${\displaystyle {\widehat {\sigma }}_{i}^{2}={\widehat {\varepsilon }}_{i}^{2}}$. This provides White's (1980) estimator, often referred to as HCE (heteroskedasticity-consistent estimator):

${\displaystyle {\begin{aligned}{\hat {\mathbb {V} }}_{\text{HCE}}{\big [}{\widehat {\boldsymbol {\beta }}}_{\text{OLS}}{\big ]}&={\frac {1}{n}}{\bigg (}{\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\bigg )}^{-1}{\bigg (}{\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\widehat {\varepsilon }}_{i}^{2}{\bigg )}{\bigg (}{\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\bigg )}^{-1}\\&=(\mathbf {X} ^{\top }\mathbf {X} )^{-1}(\mathbf {X} ^{\top }\operatorname {diag} ({\widehat {\varepsilon }}_{1}^{2},\ldots ,{\widehat {\varepsilon }}_{n}^{2})\mathbf {X} )(\mathbf {X} ^{\top }\mathbf {X} )^{-1},\end{aligned}}}$

where as above ${\displaystyle \mathbf {X} }$ denotes the matrix of stacked ${\displaystyle \mathbf {x} _{i}^{\top }}$ values from the data. The estimator can be derived in terms of the generalized method of moments (GMM).

Also often discussed in the literature (including White's paper) is the covariance matrix ${\displaystyle {\widehat {\mathbf {\Omega } }}_{n}}$ of the ${\displaystyle {\sqrt {n}}}$-consistent limiting distribution:

${\displaystyle {\sqrt {n}}({\widehat {\boldsymbol {\beta }}}_{n}-{\boldsymbol {\beta }})\,\xrightarrow {d} \,{\mathcal {N}}(\mathbf {0} ,\mathbf {\Omega } ),}$

where

${\displaystyle \mathbf {\Omega } =\mathbb {E} [\mathbf {X} \mathbf {X} ^{\top }]^{-1}\mathbb {V} [\mathbf {X} {\boldsymbol {\varepsilon }}]\operatorname {\mathbb {E} } [\mathbf {X} \mathbf {X} ^{\top }]^{-1},}$

and

${\displaystyle {\begin{aligned}{\widehat {\mathbf {\Omega } }}_{n}&={\bigg (}{\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\bigg )}^{-1}{\bigg (}{\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\widehat {\varepsilon }}_{i}^{2}{\bigg )}{\bigg (}{\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\bigg )}^{-1}\\&=n(\mathbf {X} ^{\top }\mathbf {X} )^{-1}(\mathbf {X} ^{\top }\operatorname {diag} ({\widehat {\varepsilon }}_{1}^{2},\ldots ,{\widehat {\varepsilon }}_{n}^{2})\mathbf {X} )(\mathbf {X} ^{\top }\mathbf {X} )^{-1}\end{aligned}}}$

Thus,

${\displaystyle {\widehat {\mathbf {\Omega } }}_{n}=n\cdot {\hat {\mathbb {V} }}_{\text{HCE}}[{\widehat {\boldsymbol {\beta }}}_{\text{OLS}}]}$

and

${\displaystyle {\widehat {\mathbb {V} }}[\mathbf {X} {\boldsymbol {\varepsilon }}]={\frac {1}{n}}\sum _{i}\mathbf {x} _{i}\mathbf {x} _{i}^{\top }{\widehat {\varepsilon }}_{i}^{2}={\frac {1}{n}}\mathbf {X} ^{\top }\operatorname {diag} ({\widehat {\varepsilon }}_{1}^{2},\ldots ,{\widehat {\varepsilon }}_{n}^{2})\mathbf {X} .}$

Precisely which covariance matrix is of concern is a matter of context.

Alternative estimators have been proposed in MacKinnon & White (1985) that correct for unequal variances of regression residuals due to different leverage.[11] Unlike the asymptotic White's estimator, their estimators are unbiased when the data are homoscedastic.

Of the four widely available different options, often denoted as HC0-HC3, the HC3 specification appears to work best, with tests relying on the HC3 estimator featuring better power and closer proximity to the targeted size, especially in small samples. The larger the sample, the smaller the difference between the different estimators.[12]

An alternative to explicitly modelling the heteroskedasticity is using a resampling method such as the Wild Bootstrap. Given that the studentized Bootstrap, which standardizes the resampled statistic by its standard error, yields an asymptotic refinement,[13] heteroskedasticity-robust standard errors remain nevertheless useful.

Instead of accounting for the heteroskedastic errors, most linear models can be transformed to feature homoskedastic error terms (unless the error term is heteroskedastic by construction, e.g. in a Linear probability model). One way to do this is using Weighted least squares, which also features improved efficiency properties.

• EViews: EViews version 8 offers three different methods for robust least squares: M-estimation (Huber, 1973), S-estimation (Rousseeuw and Yohai, 1984), and MM-estimation (Yohai 1987).[14]
• Julia: the CovarianceMatrices package offers several methods for heteroskedastic robust variance covariance matrices.[15]
• MATLAB: See the hac function in the Econometrics toolbox.[16]
• Python: The Statsmodel package offers various robust standard error estimates, see statsmodels.regression.linear_model.RegressionResults for further descriptions
• R: the vcovHC() command from the sandwich package.[17][18]
• RATS: robusterrors option is available in many of the regression and optimization commands (linreg, nlls, etc.).
• Stata: robust option applicable in many pseudo-likelihood based procedures.[19]
• Gretl: the option --robust to several estimation commands (such as ols) in the context of a cross-sectional dataset produces robust standard errors.[20]

• Freedman, David A. (2006). "On The So-Called 'Huber Sandwich Estimator' and 'Robust Standard Errors'". The American Statistician. 60 (4): 299–302. doi:10.1198/000313006X152207. S2CID 6222876.
• Hardin, James W. (2003). "The Sandwich Estimate of Variance". In Fomby, Thomas B.; Hill, R. Carter (eds.). Maximum Likelihood Estimation of Misspecified Models: Twenty Years Later. Amsterdam: Elsevier. pp. 45–74. ISBN 0-7623-1075-8.
• Hayes, Andrew F.; Cai, Li (2007). "Using heteroskedasticity-consistent standard error estimators in OLS regression: An introduction and software implementation". Behavior Research Methods. 39 (4): 709–722. doi:10.3758/BF03192961. PMID 18183883.
• King, Gary; Roberts, Margaret E. (2015). "How Robust Standard Errors Expose Methodological Problems They Do Not Fix, and What to Do About It". Political Analysis. 23 (2): 159–179. doi:10.1093/pan/mpu015.
• Wooldridge, Jeffrey M. (2009). "Heteroskedasticity-Robust Inference after OLS Estimation". Introductory Econometrics : A Modern Approach (Fourth ed.). Mason: South-Western. pp. 265–271. ISBN 978-0-324-66054-8.
• Buja, Andreas, et al. "Models as approximations-a conspiracy of random regressors and model deviations against classical inference in regression." Statistical Science (2015): 1. pdf