Advances in Decision Sciences

Volume 2011 (2011), Article ID 485974, 22 pages

http://dx.doi.org/10.1155/2011/485974

## Some Asymptotic Theory for Functional Regression and Classification

Department of Mathematics and Statistics, Texas Tech University, Lubbock, TX 79409, USA

Received 10 October 2011; Accepted 2 November 2011

Academic Editor: Wing Keung Wong

Copyright © 2011 Frits Ruymgaart et al. This is an open access article distributed under the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.

#### Abstract

Exploiting an expansion for analytic functions of operators, the asymptotic distribution of an estimator of the functional regression parameter is obtained in a rather simple way; the result is applied to testing linear hypotheses. The expansion is also used to obtain a quick proof for the asymptotic optimality of a functional classification rule, given Gaussian populations.

#### 1. Introduction

Certain functions of the covariance operator (such as the square root of a regularized inverse) are important components of many statistics employed for functional data analysis. If is a covariances operator on a Hilbert space, a sample analogue of this operator, and a function on the complex plane, which is analytic on a domain containing a contour around the spectrum of , a tool of generic importance is the comparison of and by means of a Taylor expansion: (It should be noted that is not in general equal to , where is the numerical derivative of ; see also Section 3.) In this paper, two further applications of the approximation in (1.1) will be given, both related to functional regression.

The first application (Section 4) concerns the functional regression estimator itself. Hall and Horowitz [1] have shown that the IMSE of their estimator, based on a Tikhonov type regularized inverse, is rate optimal. In this paper, as a complementary result, the general asymptotic distribution is obtained, with potential application to testing linear hypotheses of arbitrary finite dimension, mentioned in Cardot et al. [2] as an open problem: these authors concentrate on testing a simple null hypotheses. Cardot et al. [3] establish convergence in probability and almost sure convergence of their estimator which is based on spectral cutoff regularization of the inverse of the sample covariance operator. In the present paper, the covariance structure of the Gaussian limit will be completely specified. The proof turns out to be routine thanks to a “delta-method’’ for , which is almost immediate from (1.1).

The second application (Section 5) concerns functional classification, according to a slight modification of a method by Hastie et al. [4], exploiting penalized functional regression. It will be shown that this method is asymptotically optimal (Bayes) when the two populations are represented by equivalent Gaussian distributions with the same covariance operator. The simple proof is based on an upper bound for the norm of , which follows at once from (1.1).

Let us conclude this section with some comments and further references. The expansion in (1.1) can be found in Gilliam et al. [5], and the ensuing delta method is derived and applied to regularized canonical correlation in Cupidon et al. [6]. For functional canonical correlation see also Eubank and Hsing [7], He et al. [8], and Leurgans et al. [9]. When the perturbation ( in the present case) commutes with the expansion (1.1) can already be found in Dunford & Schwartz [10, Chapter VII], and the derivative does indeed reduce to the numerical derivative. This condition is fulfilled only in very special cases, for instance, when the random function, whose covariance operator is , is a second order stationary process on the unit interval. In this situation, the eigenfunctions are known and only the eigenvalues are to be estimated. This special case, that will not be considered here, is discussed in Johannes [11] who in particular deals with regression function estimators and their IMSE is Sobolev norms, when the regression is such a stationary process. General information about functional data analysis can be found in the monographs by Ramsay and Sliverman [12] and Ferraty and Vieu [13]. Functional time series are considered in Bosq [14]; see also Mas [15].

#### 2. Preliminaries and Introduction of the Models

##### 2.1. Preliminaries

As will be seen in the examples below, it is expedient to consider functional data as elements in an abstract Hilbert space of infinite dimension, separable, and over the real numbers. Inner product and norm in will be denoted by and , respectively. Let be a probability space, a Hilbert space valued random variable (i.e., measurable with respect to the -field of Borel sets in ), and a real valued random variable. For all that follows it will be sufficient to assume that The mean and covariance operator of will be denoted by respectively, where is the tensor product in . The Riesz representation theorem guarantees that these quantities are uniquely determined by the relations see Laha & Rohatgi [16]. Throughout is assumed to be one-to-one.

Let denote the Banach space of all bounded linear operators equipped with the norm . An operator is called Hilbert-Schmidt if for any orthonormal basis of . (The number in (2.4) is in fact independent of the choice of basis.) The subspace of all Hilbert-Schmidt operators is a Hilbert space in its own right with the inner product again independent of the choice of basis. This inner product yields the norm which is the number in (2.4). The tensor product for elements will be denoted by , and that for elements by .

The two problems to be considered in this paper both deal with cases where the best linear predictor of in terms of is linear: Just as in the univariate case (Rao [17, Section 4g]), we have the relation It should be noted that if is one-to-one and in its range, we can solve (2.8) and obtain

Since the underlying distribution is arbitrary, the empirical distribution, given a sample of independent copies of , can be substituted for it. The minimization property is now the least squares property, the same formulas are obtained with , , , and replaced with their estimators Let us next specify the two problems.

##### 2.2. Functional Regression Estimation

The model here is where is a real valued error variable and the following assumption is satisfied.

*Assumption 2.1. *The error variable has a finite second moment, and

*Example 2.2. *The functional regression model in Hall and Horowitz [1] is essentially obtained by choosing , so that the generic observation is given by

*Example 2.3. *Mas and Pumo [18] argue that in the situation of Example 2.2, the derivative of may contain important information and should therefore be included. Hence, these authors suggest to choose for the Sobolev space in which case the generic observation satisfies

*Example 2.4. *Just as in the univariate case, we have that the model
quadratic in the inner product of , is in fact linear in the inner product of , because
We will not pursue this example here.

In the infinite dimensional case cannot be one-to-one, and in order to estimate from the sample version of (2.9), a regularized inverse of Tikhonov type will be used, as in Hall & Horowitz [1]. Thus, we arrive at the estimator (see also (2.11) and (2.13)) Let us also introduce In Section 4, the asymptotic distribution of this estimator will be obtained, and the result will be applied to testing.

##### 2.3. Functional Classification

The method discussed here is essentially the one in Hastie et al. [4] and Hastie et al. [19, Sections 4.2 and 4.3]. Let and be two probability distributions on with means and and common covariance operator . Consider a random element with distribution determined by In this case, the distribution of is , with mean and covariance operator

Hastie et al. [19] now introduce the indicator response variables , , and assume that the satisfies (2.7) for and . Note that Since is Bernoulli, we have, of course, . Precisely as for matrices (Rao & Toutenburg [20, Theorem A.18]), the inverse of the operator in (2.24) equals where , provided that the following assumption is satisfied.

*Assumption 2.5. *The vector lies in the range of , that is,
It will also be assumed that

Assuming (2.28), (2.8) can be solved and yields after some algebra If only , and not , is observed, the rule in Hastie et al. [19] assigns to if and only if Because of assumption (2.29), the rule reduces to

Hastie et al. [19] claim that in the finite dimensional case, their rule reduces to Fisher’s linear discriminant rule and to the usual rule when the distributions are normal. This remains in fact true in the present infinite dimensional case. Let us assume that where denotes a Gaussian distribution with mean and covariance operator . It is well known [21–23] that under Assumption 2.5 these Gaussian distributions are equivalent. This is important since there is no “Lebesgue measure’’ on [24]. However, now the densities of and with respect to can be considered; it is well known that This leads at once to (2.33) as an optimal (Bayes) rule, equal in appearance to the one for the finite dimensional case.

In most practical situations, , , and are not known, but a training sample of independent copies of is given. Let and we have (cf. (2.24))

Once again the operator (and for that matter) cannot be one-to-one. In order to obtain an empirical analogue of the rule (2.32), Hastie et al. [4] employ penalized regression, and Hastie et al. [19] also suggest to use a regularized inverse. (The methods are related.) Here the latter method will be used and will be assigned to if and only if Section 5 is devoted to showing that this rule is asymptotically optimal when Assumption (2.5) is fulfilled.

#### 3. A Review of Some Relevant Operator Theory

It is well known [16] that the covariance operator is nonnegative, Hermitian, of finite trace, and hence Hilbert-Schmidt and therefore compact. The assumption that is one-to-one is equivalent to assuming that is strictly positive. Consequently, has eigenvalues , all of finite multiplicity. If we let be the corresponding eigenprojections, so that , we have the spectral representation:

The spectrum of equals . Let us introduce a rectangular contour around the spectrum as in Figure 1, where is the regularization parameter in (2.20), and let be the open region enclosed by . Furthermore, let be an open neighborhood of and suppose that

We are interested in approximations of , where is a perturbation. The application we have in mind arises for and yields an approximation of ; see also Watson [25] for the matrix case. Therefore, we will *not* in general assume that and will commute. In the special case where is stationary, as considered in Johannes [11], there exists a simpler estimator of , such that and do commute, which results in a simpler theory; see also Remark (4.1).

The resolvent of , is analytic on the resolvent set , and the operator is well defined. For the present operator , as given in (3.1), the resolvent equals more explicitly Substitution of (3.5) in (3.4) and application of the Cauchy integral formula yields

*Example 3.1. *The two functions
are analytic on their domain that satisfies the conditions. With the help of these functions we may write (cf. (2.20) and (2.21))
and (cf. (2.39))

Regarding the following brief summary and slight extension of some of the results in [5], we also refer to Dunford & Schwartz [10], Kato [26], and Watson [25]. Henceforth, we will assume that For such perturbations, we have , so that the resolvent set of satisfies It should also be noted that

The basic expansion (similar to Watson [25]) can be written as useful for analyzing the error probability for , as , and also as useful for analyzing the convergence in distribution of the estimators.

Let us decompose the contour into two parts and , write , and observe that (3.10) and (3.12) entail that We now have Multiplying both sides by , taking , and using as a generic constant that does not depend on or , (3.14) and (3.15) yield the following.

Theorem 3.2. *Provided that (3.10) is fulfilled, one has
**
where is a bounded operator, given by
*

*Remark 3.3. *If and commute, so will and , and and , and the expressions simplify considerably. In particular, (3.20) reduces to
that is, , where is the numerical derivative of , and should be understood in the sense of “functional calculus’’ as in (3.6). For the commuting case, see Dunford & Schwartz [10].

Let us now present some basic facts that are useful to subsequent statistical applications. Dauxois et al. [27] have shown that there exists a Gaussian random element , such that , as , in . Because the identity map from in is continuous, we may state by the continuous mapping theorem. This entails that so that condition (3.10) is fulfilled with arbitrary high probability for sufficiently large. Expansions (3.14) and (3.15) and the resulting inequalities hold true for replaced with for .

*Example 3.4. *Application to asymptotic distribution theory. In this application will be kept fixed: see also Section 4.1. It is based on the delta method for functions of operators [6] which follows easily from (3.19). In conjunction with (3.22) this yields
In turn this yields
for any , by the continuous mapping theorem. This result will be used in Section 4.

*Example 3.5. *Application to classification. Here we will let , as , and write to stress this dependence on sample sizes. Since
it is immediate from (3.18) that
a result that will be used in Section 5.

#### 4. Asymptotics for the Regression Estimator

##### 4.1. The Asymptotic Distribution

The central limit theorem in Hilbert spaces entails at once where is a zero mean Gaussian random variable in , and where is a zero mean random variable in . These convergence results remain true with replaced by and, because by assumption (2.15), we also have that jointly where is the same in (3.22), and

Because the limiting variables are generated by the sums of iid variables on the left in (4.1) and (4.2) we have for the respective covariance structures. These are important to further specify the limiting distribution of the regression estimator as will be seen in Section 4.2.

Let us write, for brevity, where, according to (2.20) and (2.21), Note that and depend on .

With statistical applications in mind, it would be interesting if there would exist numbers and , as , such that where is a nondegenerate random vector. It has been shown in Cardot et al. [28], however, that such a convergence in distribution when we center at is not in general possible.

Theorem 4.1. *For fixed , one has
**
where and are zero mean Gaussian random elements, and .*

Further information about the structure of the covariance operator of the random vector on the right in (4.10) will be needed in order to be able to exploit the theorem for statistical inference. This will be addressed in the next section.

##### 4.2. Further Specification of the Limiting Distribution

It follows from (4.5) that has a Karhunen-Loève expansion where the real valued random variables Accordingly in (4.10) can be further specified as

The Gaussian operator in (4.2) has been investigated in Dauxois et al. [27], and here we will briefly summarize some of their results in our notation. By evaluating the inner product in in the basis it follows from (4.6) that

This last expression does not in general further simplify. However, if we assume that the regressor satisfies it can be easily seen that the so that the expression in (4.14) equals zero if . As in Dauxois et al. [27], we obtain in this case where

Consequently the are an orthonormal basis of eigenvectors of the covariance operator of with eigenvalues . Hence has the Karhunen-Loève expansion (in ) where the random variables

Let us, for brevity, write (see (3.7) for ) Summarizing, we have the following result.

Theorem 4.2. *The random element , on the right in (4.10) can be represented by (4.13). If one assumes that the regressor , the random element on the right in (4.10) can be represented by (4.22), where the in (4.20) are stochastically independent of the in (4.12).*

##### 4.3. Asymptotics under the Null Hypothesis

Let us recall that is related to according to (2.21) so that the equivalence where again is fixed, holds true. The following is immediate from Theorem 4.1.

Theorem 4.3. *Under the null hypothesis in (4.23), one has
**
where
*

An immediate generalization of the hypothesis in (4.23) is for some given . This hypothesis is in principle of interest for confidence sets. Of course, testing (4.26) can be reduced to testing (4.23) by replacing the with and then using the estimator Since the following is immediate.

Theorem 4.4. *Assuming (4.27), one has
**
where has the same distribution as in (4.25). Related results can be found in Cardot et al. [2].*

Another generalization of the hypothesis in (4.23) is where are orthonormal vectors in . Let and denote the orthogonal projection onto and respectively, and note that if and only if . A test statistic might be based on and we have the following.

Theorem 4.5. *Under in (4.30), one has
*

The distribution on the right in (4.31) is rather complicated if remain arbitrary. But if we are willing to assume (4.20), it follows from (4.27) that

A simplification is possible if we are willing to modify the hypothesis in (4.30) and use a so-called neighborhood hypothesis. This notion has a rather long history and has been investigated by Hodges & Lehmann [29] for certain parametric models. Dette & Munk [30] have rekindled the interest in it by an application in nonparametric regression. In the present context we might replace (4.30) with the neighborhood hypothesis It is known from the literature that the advantage of using a neighborhood hypothesis is not only that such a hypothesis might be more realistic and that the asymptotics are much simpler, but also that without extra complication we might interchange null hypothesis and alternative. This means in the current situation that we might as well test the null hypothesis which could be more suitable, in particular in goodness-of-fit problems.

The functional , , has a Fréchet derivative at given by the functional , . Therefore, the delta method in conjunction with Theorem 4.1 entails the following result.

Theorem 4.6. *One has
*

The limiting distribution on the right in (4.35) is normal with mean zero and complicated variance

*Remark 4.7. *As we see from the expressions in (4.24), (4.32), and (4.36), the limiting distributions depend on infinitely many parameters that must be suitably estimated in order to be in a position to use the statistics for actual testing. Estimators for the individual parameters are not too hard to obtain. The eigenvalues and eigenvectors of , for instance, can in principle be estimated by the corresponding quantities of . Although in any practical situation only a finite number of these parameters can be estimated, theoretically this number must increase with the sample size and some kind of uniform consistency will be needed for a suitable approximation of the limiting distribution. This interesting question of uniform consistency seems to require quite some technicalities and will not be addressed in this paper.

*Remark 4.8. *In this paper we have dealt with the situation where is entirely unknown. It has been observed in Johannes [11] that if is a stationary process on the unit interval, the eigenfunctions of the covariance operator are always the same, known system of trigonometric functions, and only its eigenvalues are unknown. Knowing the leads to several simplifications. In the first place, can now be estimated by the expression on the right in (3.1) with only the replaced with estimators. If is this estimator, it is clear that and commute, so that the derivative now simplifies considerably (see Remark 3.3). Secondly, we might consider the special case of in (4.30), where , . We now have
so that even for fixed we can test the actual regression function. In the third place, under the null hypothesis in (4.37), the number of unknown parameters in (4.32) reduces considerably because now for . When the are known, in addition to all the changes mentioned above, also the limiting distribution of differs from that of . Considering all these modifications that are needed, it seems better not to include this important special case in this paper.

##### 4.4. Asymptotics under Local Alternatives

Again we assume that is Gaussian. Suppose that For such only minor changes in the asymptotics are required, because the conditions on the and are still the same and do not change with . Let us write where , . The following is immediate from a minor modification of Theorem 4.1.

Theorem 4.9. *For as in (4.39), one has
**
where is the same as in (4.13), is obtained from in (4.22) by replacing with , and .*

By way of an example, let us apply this result to testing the neighborhood hypothesis and consider the asymptotics of the test statistics in (4.35) under the local alternatives in (4.39) with

Note that under such alternatives, is still a consistent estimator of for any , as , and so is for . The following is immediate from Theorem 4.9. To conclude this section, let us first assume that parameters can be suitably estimated. We then arrive at the limiting distribution of a test statistics that allows the construction of an asymptotic level- test whose asymptotic power can be computed.

Theorem 4.10. *For , as in (4.40) and (4.41), one has
**
assuming that is a consistent estimator of in (4.36). Note that the limiting distribution is under (i.e., ).*

#### 5. Asymptotic Optimality of the Classification Rule

In addition to Assumption 2.5 and (2.34), it will be assumed that the smoothness parameter in (2.39) satisfies We will also assume that the sizes of the training samples and (see (2.36)) are deterministic and satisfy () Let us recall from (3.7) that .

Under these conditions the probability of misclassification equals . Let us note that Since , , and, according to (3.21), it follows from (5.1) that the limit of the misclassification probability equals where is the standard normal cdf.

For (5.5) we have used the well-known property of regularized inverses that , as , for all , and the fact that we may choose by Assumption 2.5. Since rule (2.33) is optimal when parameters are known, we have obtained the following result.

Theorem 5.1. *Let and let Assumption 2.5 and (5.1) be satisfied. Then the classification rule (2.39) is asymptotically optimal.*

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