The Neyman-Pearson lemma and the Durbin-Watson test

The first formal specification test in econometrics, the Durbin-Watson (DW) (1950) test for autocorrelation in the regression model has its foundation in the UMP test principle via a theorem of Anderson (1948). Most econometrics textbooks provide a detail discussion of the DW test but do not mention its origin. Let us consider the standard linear regression model with autocorrelated errors:

Vt = 4е + et (2.54)

£t = pet-1 + Ut, (2.55)

where Vt is the tth observation on the dependent variable, xt is the tth observation on k strictly exogenous variables, | p | < 1 and ut ~ iidN(0, о2), t = 1, 2,…, n. The problem is testing H0 : p = 0. Using the N-P lemma, Anderson (1948) showed that UMP tests for serial correlation can be obtained against one-sided alternatives.7 A special case of Anderson’s lemma is as follows:

If the probability density of e can be written in the form,

2^1(1 + р2)є’є – 2рє’Оє}

 

f (є) = const. exp

 

(2.56)

 

where e = (e 1, e 2,……. en)’ and columns of X = (x1, x2,…, xn) are generated

by k eigen-vectors of D, the UMP test of H0 : p = 0 against H1 : p > 0 is given by a > a0, where

e ‘De

є ‘є,

and a0 is such that Pr[a > a0| p = 0] = a, the size of the test. Here є = (єа, є2,…, єn)’ with et = yt – xtS and S is the ordinary least squares (OLS) residual vector.

For the model given in (2.54) and (2.55), the probability distribution of e, that is, the likelihood function is given by8

— f(1 + р2)є’є – р2(є[5] [6] + є

image099

const. exp

 

(2.58)

 

image100

Comparing (2.56) and (2.58), we see that the latter cannot be written in the form of the former. Durbin and Watson (1950) approached the problem from the opposite direction and selected a form of D in such a way that (2.56) becomes "close" to (2.58). They chose D = In – | A, where

Подпись: " 1 -1 0 0 L 0 0 0 -1 2 -1 0 L 0 0 0 А = 0 -1 2 -1 ... 0 0 0 0 0 0 0 -1 2 -1 _ 0 0 0 0. 0 -1 1 (2.59)

so that

n n

є^є = Хє2 – 2 X(^ – єм)2

t=1 2 t=2

Подпись:Подпись:= т^(єі + єП ) + X єієі-і – Then, the density (2.56) reduces to

1 f n

/(є) = const. exp – — f (1 + р2)є’є – р(є2і + єП) – 2pX є, Є,-і

Now the only difference between the likelihood function (2.58) and (2.61) is on the middle terms involving p2 and p, and the difference can be neglected. Anderson’s theorem suggests that a UMP test should be based on

є’є – І єАє
є’є

 

image104
image105 Подпись: (2.63)

Durbin and Watson (1950) used a slight transformation of "a" to form their test statistic, namely,

image107 Подпись: (2.64)

Note that "a" in (2.62) is approximately equal to the estimate p = ХП=2 є te t-1/X[t1є?, whereas d — 2(1 – p). Most econometrics textbooks discuss in details about tables of bounds for the DW test, and we will not cover that here. Our main purpose is to trace the origin of the DW test to the N-P lemma. For a historical account of the DW test, see (King, 1987). In spatial econometrics, Moran’s (1950) test for spatial dependence has the similar form

where W is a spatial weight matrix that represents "degree of potential interac­tion" among neighboring locations. Using the above analysis it is easy to link I to the N-P lemma and demonstrate its optimality [for more on this, see (Anselin and Bera, 1998)].

3.1 Use of score test in econometrics

In the econometrics literature, Rao’s score test is known as the Lagrange multi­plier test. This terminology came from Silvey (1959). Note that the restricted MLE of 0 under the restriction H0 : h(0) = c can be obtained from the first order condition of the Lagrangian function

L = l(0) – X'[h(0) – c], (2.65)

where X is an r x 1 vector of Lagrange multipliers. The first order conditions are

s(0) – H(0)X = 0 (2.66)

h(0) = c, (2.67)

where H(0) = . Therefore, we have s(0) = H(0)X. Given that H(0) has full rank,

s(0) = 0 is equivalent to X = 0, that is, the Lagrange multipliers vanish. These multipliers can be interpreted as the implicit cost (shadow prices) of imposing the restrictions. It can be shown that

Подпись:X = dl(R),

dc

that is, the multipliers give the rate of change of the maximum attainable value with respect to the change in the constraints. If H0 : h(0) = c is true and 1(0) gives the optimal value, X should be close to zero. Given this "economic" interpretation in terms of multipliers, it is not surprising that econometricians prefer the term LM rather than RS. In terms of Lagrange multipliers, (2.39) can be expressed as

RS = LM = X’H(0)’I (0)-1H(0)X. (2.69)

Byron (1968), probably the first to apply the RS test in econometrics, used the version (2.69) along with the LR statistic for testing homogeneity and symmetry restrictions in demand equations. It took another decade for econometricians to realize the potential of the RS test. In this regard, the work of Breusch and Pagan

(1980) has been the most influential. They collected relevant research reported in the statistics literature, presented the RS test in a general framework in the con­text of evaluating econometric models, and discussed many applications. Since the late 1970s, econometricians have applied the score principle to a variety of econometric testing problems and studied the properties of the resulting tests. Now the RS tests are the most common items in the econometricians’ kit of testing tools. We will make no attempt to provide a test of all applications of the RS test in econometrics for these are far too many. For example, consider the linear regression model (2.54). The OLS analysis of this model is based on four basic assumptions: correct linear functional form; the assumptions of disturbance normality; homoskedasticity; and serial independence. Violation of these affects both estimation and inference results. With the aid of the RS principle, many procedures have been proposed to test the above assumptions and these are now routinely reported in most of the standard econometric software packages. In most cases, the algebraic forms of the LR and W tests can hardly be simplified beyond their original formulae (2.12) and (2.40). On the other hand, in many cases the RS test statistics, apart from its computational ease, can be reduced to neat and elegant formulae enabling its easy incorporation into computer soft­ware. Breusch and Pagan (1980), Godfrey (1988), Bera and Ullah (1991), Davidson and MacKinnon (1993), and Bera and Billias (2000) discussed many applications of the score tests in econometrics and demonstrated that many of the old and new econometric tests could be given a score-test interpretation. For example, test procedures developed in Hausman (1978), Newey (1985), Tauchen (1985), and White (1982) could be put in the framework of the score test. To see this, let us consider the Newey (1985) and Tauchen (1985) moment test and write the moment restriction as

Ef[m(y; 0)] = 0, (2.70)

where Ef means that (2.70) is true only whenf(y; 0) is the correct p. d.f. A test for this hypothesis can be based on the estimate of the sample counterpart of (2.70), namely,

1 n

X m( у ; 0).

n и

Now consider an auxiliary p. d.f.

f *(y; 0. Y) = f (y; 0) exp[ym(y; 0) – ф(Є, у)], (2.72)

where ф(0, у) = ln/ехр[уш(y; 0)]f(y; 0)dy. Note that if f(y; 0) is the correct p. d.f., then у = 0 in (2.72). Therefore, a test for the correct specification of f( y; 0) can be achieved by testing у = 0. Writing the loglikelihood function under the alternative hypothesis as

l*(0, y) = Xln f*( y; 0, y).

і=1

dl*(0, y)

Подпись: dY Подпись: Y=0 Подпись: X m( y<; 0). i =1 Подпись: (2.73)

we see that the score function for testing у = 0 in (2.72) is

and it gives the identical moment test. This interpretation of the moment test as a score test was first noted by White (1984). Recently, Chesher and Smith (1997) gave more general and rigorous treatments of this issue. There are uncountably many choices of the auxiliary p. d.f. f *( y; 0, у), and the score test is invariant with respect to these choices. The LR test, however, will be sensitive to the form of

f*( y; 0 у).

Neyman’s (1959) C(a) formulation, which formally established that "every" locally optimal test should be based on the score function (see equation (2.47)), also has been found to be useful in econometrics. For testing complicated nonlinear restrictions the Wald test has a computational advantage; however, on this par­ticular occasion the Wald test runs into a serious problem of non-invariance, as pointed out by Gregory and Veal (1985) and Vaeth (1985). In this situation the score tests are somewhat difficult to compute, but the C(a) tests are the most convenient to use, as demonstrated by Dagenais and Dufour (1991) and Bera and Billias (2000).

Rayner and Best (1989, sections 4.2 and 6.1) showed that Neyman’s smooth statistic у) in (2.35) can be derived as a score test for testing H0 : 51 = S2 = … = 5r = 0 in (2.33). In fact, Neyman’s smooth test can be viewed as a first formally derived Rao’s score test from the Neyman-Pearson principle. We have seen no formal application of the smooth test in econometrics. However, Lawrence Klein gave a seminar on this topic at MIT during academic year 1942-3 to draw atten­tion to Neyman (1937), since the paper was published in a rather recondite jour­nal [see Klein, 1991]. Unfortunately, Klein’s effort did not bring Neyman’s test to econometrics. However, some of the tests in econometrics can be given a smooth test interpretation. The test for normality suggested in Jarque and Bera (1980) and Bera and Jarque (1981) can be viewed as a smooth test [see Rayner and Best, 1989, p. 90]. Orthogonal polynomial tests suggested by Smith (1989) and Cameron and Trivedi (1990) are also in the spirit of Neyman (1937). In a recent paper

Diebold, Gunther, and Tay (1998) suggested the use of the density of the prob­ability integral transformation (2.31) for density forecast evaluation. They adopted a graphical approach; however, their procedure can be formalized by using a test of the form у2.

In Example 3 we saw that the score function vanished under the null hypoth­esis. In economics this kind of situation is encountered often [see, for instance, Bera, Ra, and Sarkar, 1998]. Lee and Chesher (1986) have offered a comprehen­sive treatment of this problem, and one of the examples they considered is the stochastic production frontier model of Aigner, Lovell, and Schmidt (1977). In Lee and Chesher (1986) the score vanished when they tried to test the null hy­pothesis that all the firms are efficient. They suggested using the second-order derivatives of the loglikelihood function. From (2.25) we get the same test prin­ciple by putting s(00) = 0, namely, reject the null if

Therefore, again using the Neyman-Pearson principle, we see that when the score vanishes, we cannot get a locally best test but we can obtain a locally best unbiased test based on the second derivative of the loglikelihood function.

4 Epilogue

In this chapter we have first explored the general test principles developed by statisticians with some simple examples and, then, briefly discussed how those principles have been used by econometricians to construct tests for econometric models. It seems we now have a large enough arsenal to use for model testing. We should, however, be careful particularly about two aspects of testing: first, interpreting the test results, and second, taking the appropriate action when the null hypothesis is rejected. When asked about his contribution to linear models, Geoff Watson mentioned the DW test but added [see Beran and Fisher, 1998, p. 91], "What do I do if I have a regression and find the errors don’t survive the Durbin-Watson test? What do I actually do? There is no robust method. You’d like to use a procedure that would be robust against errors no matter what the covariance matrix is. Most robustness talk is really about outliers, long-tail ro­bustness. Dependence robustness is largely untouched."9 This problem can arise after applying any test. Use of large sample tests when we have very limited data and the issue of pretesting are other important concerns. As this century and the millennium rush to a close, more research to solve these problems will make econometric model evaluation and testing more relevant in empirical work.

Notes

* We would like to thank Badi Baltagi, Roger Koenker and two anonymous referees for many pertinent comments. We are also grateful to Yulia Kotlyarova who provided very competent research assistance during the summer of 1998 and offered many helpful suggestions on an earlier draft of this chapter. We, however, retain the responsibility for any remaining errors. Financial support from the Research Board of the University of Illinois at Urbana-Champaign and the Office of Research, College of Commerce and Business Administration, University of Illinois at Urbana-Champaign are gratefully acknowledged.

1 Neyman (1980, p. 6) stated their intuition as, "The intuitive background of the likelihood ratio test was simply as follows: if among the contemplated admissible hypotheses there are some that ascribe to the facts observed probabilities much larger than that ascribed by the hypothesis tested, then it appears ‘reasonable’ to reject the hypothesis."

2 This result follows from the generalized Cauchy-Schwarz inequality (Rao, 1973, p. 54)

(u’v)2 < (u’Au)(v‘A-1v),

where u and v are column vectors and A is a non-singular matrix. Equality holds when

u = A-1v.

3 The interrelationships among these three tests can be brought home to students through an amusing story. Once around 1946 Ronald Fisher invited Jerzy Neyman, Abraham Wald, and C. R. Rao to his lodge for afternoon tea. During their conversation, Fisher mentioned the problem of deciding whether his dog, who had been going to an "obe­dience school" for some time, was disciplined enough. Neyman quickly came up with an idea: leave the dog free for some time and then put him on his leash. If there is not much difference in his behavior, the dog can be thought of as having completed the course successfully. Wald, who lost his family in the concentration camps, was adverse to any restrictions and simply suggested leaving the dog free and seeing whether it behaved properly. Rao, who had observed the nuisances of stray dogs in Calcutta streets, did not like the idea of letting the dog roam freely and suggested keeping the dog on a leash at all times and observing how hard it pulls on the leash. If it pulled too much, it needed more training. That night when Rao was back in his Cambridge dormitory after tending Fisher’s mice at the genetics laboratory, he suddenly realized the connection of Neyman and Wald’s recommendations to the Neyman-Pearson LR and Wald tests. He got an idea and the rest is history.

4 In the C(a) test the letter "C" refers to Cramer and "a" to the level of significance. Neyman (1959) was published in a Festschrift for Harald Cramer. Neyman frequently referred to this work as his "last performance." He was, however, disappointed that the paper did not attract as much attention as he had hoped for, and in later years, he regretted publishing it in a Festschrift as not many people read Festschrifts.

5 In the introduction (p. 11), Tinbergen stated,

The purpose of this series of studies is to submit to statistical test some of the theories which have been put forward regarding the character and causes of cyclical fluctuation in business activity. Many of these theories, however, do not exist in a form immediately appropriate for statistical testing while most of them take account of the same body of economic phenom­ena – viz., the behavior of investment, consumption, incomes, prices, etc. Accordingly, the method of procedure here adopted is not to test the various theories one by one (a course which would involve much repetition), but to examine in succession, in the light of the various explanations which have been offered, the relation between certain groups of eco­nomic phenomena.

He, however, cautioned against relying too much on the test results, "for no statist­ical test can prove a theory to be correct" (p. 12). For more on this see (Duo, 1993, Chapter 5).

6 In his Nobel lecture he stated (Haavelmo, 1997),

“For my own part I was lucky enough to be able to visit the United States in 1939 on a scholarship…. I then had the privilege of studying with the world famous statistician Jerzy Neyman in California for a couple of months. At that time, young and naive, I thought I knew something about econometrics. I exposed some of my thinking on the subject to Professor Neyman. Instead of entering into a discussion with me, he gave me two or three exercises for me to work out. He said he would talk to me when I had done these exercises. When I met him for the second talk, I had lost most of my illusions regarding the understanding of how to do econometrics. But Professor Neyman also gave me hopes that there might be other more fruitful ways to approach the problem of econometric methods than those which had so far caused difficulties and disappointments.”

7 Technically speaking, this model does not fit in our earlier framework due to the dependence structure. However, once a proper likelihood function is defined we can derive our earlier test statistics.

8 Instead of dealing with the joint distribution conditional on the explanatory variables in all time periods, a better approach would be to consider sequential conditional distribution under much weaker assumptions. Wooldridge (1994) discusses the merits of modeling sequential distributions.

9 We should, however, note that econometricians have developed a number of proce­dures to estimate a consistent variance-covariance matrix to take account of the un­known form of dependence; for a discussion of this and other robust procedures see (Bera, 2000) and (Wooldridge, 2000).

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