A robust approach to model-based classification based on trimming and constraints Semi-supervised learning in presence of outliers and label noise

A robust approach to model-based classification based on trimming and constraints
Semi-supervised learning in presence of outliers and label noise

Andrea Cappozzo111Department of Statistics and Quantitative Methods, University of Milano-Bicocca, a.cappozzo@campus.unimib.it, francesca.greselin@unimib.it    Francesca Greselinfootnotemark:    Thomas Brendan Murphy222School of Mathematics & Statistics and Insight Research Centre, University College Dublin, brendan.murphy@ucd.ie

In a standard classification framework a set of trustworthy learning data are employed to build a decision rule, with the final aim of classifying unlabelled units belonging to the test set. Therefore, unreliable labelled observations, namely outliers and data with incorrect labels, can strongly undermine the classifier performance, especially if the training size is small. The present work introduces a robust modification to the Model-Based Classification framework, employing impartial trimming and constraints on the ratio between the maximum and the minimum eigenvalue of the group scatter matrices. The proposed method effectively handles noise presence in both response and exploratory variables, providing reliable classification even when dealing with contaminated datasets. A robust information criterion is proposed for model selection. Experiments on real and simulated data, artificially adulterated, are provided to underline the benefits of the proposed method.

1 Introduction

In statistical learning, we define classification as the task of assigning group memberships to a set of unlabelled observations. Whenever a labelled sample (i.e., the training set) is available, the information contained in such dataset is exploited to classify the remaining unlabelled observations (i.e., the test set), either in a supervised or in a semi-supervised manner, depending whether the information contained in the test set are included in building the classifier (e.g. McNicholas, 2016). Either way, the presence of unreliable data points can be detrimental for the classification process, especially if the training size is small (Zhu and Wu, 2004).

Broadly speaking, noise is anything that obscures the relationship between the attributes and the class membership (Hickey, 1996). In a classification context, Wu (1995) distinguishes between two types of noise: attribute noise and class noise. The former is related to contamination in the exploratory variables, that is when observations present unusual values on their predictors; whereas the latter refers to samples whose associated labels are wrong. Zhu and Wu (2004) and the recent work of Prati et al. (2018) offer an extensive review on the topic and the methods that have been proposed in the literature to deal with attribute noise and class noise, respectively. Generally, three main approaches can be employed when building a classifier from a noisy dataset: cleaning the data, modeling the noise and using robust estimators of model parameters (Bouveyron and Girard, 2009).

The approach presented in this paper is based on a robust estimation of a Gaussian mixture model with parsimonious structure, to account for both attribute and label noise. Our conjecture is that the contaminated observations would be the least plausible units under the robustly estimated model: the corrupted subsample will be revealed by detecting those observations with the lowest contributions to the associated likelihood. Impartial trimming (Gordaliza, 1991a, b; Cuesta-Albertos et al., 1997) is employed for robustifying the parameter estimates, being a well established technique to treat mild and gross outliers in the clustering literature (García-Escudero et al., 2010) and here used, for the first time, to additionally account for label noise in a classification framework. A semi-supervised approach is developed, where information contained in both labelled and unlabelled samples is combined for improving the classifier performance and for defining a data-driven method to identify outlying observations possibly present in the test set.

The rest of the manuscript is organized as follows. A brief review on model-based discriminant analysis and classification is given in Section 2, Section 3 introduces the robust updating classification rules, covering the model formulation, inference aspects and model selection. A simulation study to compare the method introduced in Section 3 with other popular model-based classification methods is reported in Section 4. Finally, in Section 5 our proposal is employed in performing classification and adulteration detection in a food authenticity context, dealing with contaminated samples of Irish honey. Concluding notes and further research directions are outlined in Section 6.

2 Model-Based Discriminant Analysis and Classification

In this Section we review the main concepts of supervised classification based on mixture models, with particular focus on Eigenvalue Decomposition Discriminant Analysis and its semi-supervised formulation, as introduced in Dean et al. (2006). This approach is the basis of the novel robust semi-supervised classifier introduced in Section 3.

2.1 Eigenvalue Decomposition Discriminant Analysis

Model-based discriminant analysis (McLachlan, 1992; Fraley and Raftery, 2002) is a probabilistic approach for supervised classification, in which a classifier is built from a complete set of learning observations ; where and , , are independent realizations of random vectors and , respectively. That is, denotes a -variate observation and its associated class label, such that if observation belongs to group and otherwise, . Considering a Gaussian framework, the probabilistic mechanism that is assumed to have generated the data is as follows:


where is multinomially distributed with probability of observing class and the conditional density of given is multivariate normal with mean vector and variance covariance matrix . Therefore, the joint density of is given by:


where denotes the multivariate normal density and represents the collection of parameters to be estimated, . Discriminant analysis makes use of data with known labels to estimate model parameters for creating a classification rule. The trained classifier is subsequently employed for assigning a set of unlabelled observations , to the class with the associated highest posterior probability:


using the maximum a posteriori (MAP) rule. The afore-described framework is widely employed in classification tasks, thanks to its probabilistic formulation and well-established efficacy.

The number of parameters in the component variance covariance matrices grows quadratically with the dimension . Thus, Bensmail and Celeux (1996) introduced a parsimonious parametrization proposing to enforce additional assumptions on the matrices structure, based on the eigen-decomposition of Banfield and Raftery (1993) and Celeux and Govaert (1995):


where is an orthogonal matrix of eigenvectors, is a diagonal matrix such that and . This elements correspond respectively to the orientation, shape and volume (alternatively called scale) of the different Gaussian components. Allowing each parameter in (4) to be equal or different across groups, Bensmail and Celeux (1996) define a family of 14 patterned models, listed in Table 1. Such class of models is particularly flexible, as it includes very popular classification methods like Linear Discriminant Analysis and Quadratic Discriminant Analysis as special cases for the EEE and VVV models, respectively (Hastie and Tibshirani, 1996). Eigenvalue Decomposition Discriminant Analysis (EDDA) is implemented in the mclust R package (Fop et al., 2016).

Model Volume Shape Orientation
EII Equal Spherical - -
VII Variable Spherical - -
EEI Equal Equal Axis-aligned -
VEI Variable Equal Axis-aligned -
EVI Equal Variable Axis-aligned -
VVI Variable Variable Axis-aligned -
EEE Equal Equal Equal
VEE Variable Equal Equal
EVE Equal Variable Equal
EEV Equal Equal Variable
VVE Variable Variable Equal
VEV Variable Equal Variable
EVV Equal Variable Variable
VVV Variable Variable Variable
Table 1: Nomenclature, covariance structure and number of free parameters in : denotes the number of parameters related to the orthogonal rotation and the number of parameters related to the eigenvalues.

2.2 Updating Classification Rules

Exploiting the assumption that the data generating process outlined in (1) is the same for both labelled and unlabelled observations, Dean et al. (2006) propose to include also the data whose memberships are unknown in the parameter estimation. That is, information about group structure that may be contained in both labelled and unlabelled samples is combined in order to improve the classifier performance, in a semi-supervised manner.

Under the framework defined in Section 2.1, and given the set of available information , , the observed log-likelihood is


in which both labelled and unlabelled samples are accounted for in the likelihood definition. Treating the (unknown) labels , , as missing data and including them in the likelihood specification defines the so called complete-data log-likelihood:


Maximum likelihood estimates for (5) are obtained through the EM algorithm (Dempster et al., 1977), iteratively computing the expected value for the unknown labels given the current set of parameter estimates (E-Step), and employing (6) to find maximum likelihood estimates for the unknown parameters (M-Step). The unlabelled data are then classified according to , using the MAP. The updating classification rules was demonstrated to give improved classification performance over the classical model-based discriminant analysis in some food authenticity applications, particularly when the training size is small. An implementation of this can be found in the upclass R package (Russell et al., 2014).

3 Robust Updating Classification Rules

We introduce here a Robust modification to the Updating Classification Rule described in Section 2.2, with the final aim of developing a classifier whose performance is not affected by contaminated data, either in the form of label noise and outlying observations.

3.1 Model Formulation

The main idea of the proposed approach is to employ techniques originated in the branch of robust statistics to obtain a model-based classifier in which parameters are robustly estimated and outlying observations identified. We are interested in providing a method that jointly accounts for noise on response and exploratory variables, where the former might be present in the labelled set and the latter in both the labelled and unlabelled sets. We propose to modify the log-likelihood in (5) with a trimmed mixture log-likelihood (Neykov et al., 2007) and to employ impartial trimming and constraints on the covariance matrices for achieving both robust parameter estimation and identification of the unreliable sub-sample. Impartial trimming is enforced by considering the distinct structure of the likelihoods associated to the labelled and unlabelled sets, accounting for the possible label noise that might be present in the labelled sample (see Section 3.2 for details). Following the same notation introduced in Section 2.1, we aim at maximizing the trimmed observed data log-likelihood:


where , are 0-1 trimming indicator functions, that express whether observation and are trimmed off or not. A fixed fraction and of observations, belonging to the labelled and unlabelled set respectively, is unassigned by setting and . In this way, the less plausible samples under the currently estimated model are tentatively trimmed out at each step of the iterations that leads to the final estimate. The labelled trimming level and the unlabelled trimming level account for possible adulteration in both sets. At the end of the iterations, a value of or corresponds to identify or , respectively, as unreliable observations. Notice that impartial trimming automatically deals with both class noise and attribute noise, as observations that suffer from either noise structure will give low contribution to the associated likelihood.

Maximization of (7) is carried out via the EM algorithm, in which an appropriate Concentration Step (Rousseeuw and Driessen, 1999) is performed in both labelled and unlabelled sets at each iteration to enforce the impartial trimming. In addition, we protect the parameter estimation from spurious solutions, that may arise whenever one component of the mixture fits a random pattern in the data. We consider the eigenvalue-ratio restriction:


where and , with , being the eigenvalues of the matrix and being a fixed constant (Ingrassia, 2004). Constraint (8) simultaneously controls differences between groups and departures from sphericity, by forcing the relative length of the axes of the equidensity ellipsoids, based on the multivariate normal distribution, to be smaller than (García-Escudero et al., 2014). Notice that the constraint in (8) is still needed whenever either the shape or the volume is free to vary across components (García-Escudero et al., 2017), that is for all models in Table 1 for which the Volume and/or Shape columns have “Variable” entries. Feasible and computationally efficient algorithms for enforcing the eigen-ratio constraint for different patterned models are reported in the Appendix.

3.2 Estimation Procedure

The EM algorithm for obtaining Maximum Trimmed Likelihood Estimates of the robust updating classification rule involves the following steps:

  • Initialization: set . The starting values are obtained via standard Eigenvalue Decomposition Discriminant Analysis (see Section 2.1). That is, find , and using only the labelled data. This can be performed using MclustDA routine in the mclust package. If the selected patterned model allows for heteroscedastic and (8) is not satisfied, constrained maximization is enforced, see the Appendix for details.

  • EM Iterations: denote by the parameter estimates at the -th iteration of the algorithm.

    • Step 1 - Concentration: the trimming procedure is implemented by discarding the observations with smaller values of


      and discarding the observations with smaller values of

    • Step 2 - Expectation: for each non-trimmed observation compute the posterior probabilities

    • Step 3 - Constrained Maximization: the parameter estimates are updated, based on the non-discarded observations and the current estimates for the unknown labels:


      Estimation of depends on the considered patterned model and on the eigenvalues-ratio constraint. Details are given in Bensmail and Celeux (1996) and, if (8) is not satisfied, in the Appendix.

    • Step 4 - Convergence of the EM algorithm: check for algorithm convergence (see Section 3.3). If convergence has not been reached, set and repeat steps 1-4.

Notice how the trimming step differs between the labelled and unlabelled observations. We implicitly assume that a label in the training set conveys a sound meaning about the presence of a class of objects. Therefore, in the labelled set, we opted for trimming the samples with lowest conditional density . The alternative choice of considering the joint density is instead prone to trim off completely groups with small prior probability for large enough value of , and should be discarded. Note that with (9) we are both discriminating label noise (i.e., observations that are likely to belong to the mixture model but whose associated label is wrong) and outliers. In the unlabelled set, on the other hand, trimming is based on the marginal density , having no prior information on the group membership of the samples.

Once convergence is reached, the estimated values provide a classification for the unlabelled observations , assigning observation into group if for all . Final values of , and , classify and respectively, as outlying observations.

The routines for estimating the robust updating classification rules have been written in R language (R Core Team, 2018). The source code is available from the authors upon request, and an R package is currently under development.

3.3 Convergence Criterion

We assess whether the EM algorithm has reached convergence evaluating at each iteration how close the trimmed log-likelihood is to its estimated asymptotic value, using the Aitken acceleration (Aitken, 1926):


where is the trimmed observed data log-likelihood from iteration . The asymptotic estimate of the trimmed log-likelihood at iteration is given by (Bohning et al., 1994):


The EM algorithm is considered to have converged when ; a value of has been chosen for the experiments reported in the next Sessions.

Figure 1: Simulated data considering the Simulation Setup described in Section 4.1, varying Contamination Rate

3.4 Model Selection

A robust likelihood-based criterion is employed for choosing the best model among the 14 patterned covariance structures listed in Table 1 and a reasonable value for the constraint in (8):


where denotes the maximized trimmed observed data log-likelihood and a penalty term whose definition is:


That is, depends on the total number of parameters to be estimated: and for every patterned model are given in Table 1. It also accounts for the trimming levels and for the eigen-ratio constraint , according to Cerioli et al. (2018). Note that, when and , (16) is the Bayesian Information Criterion (Schwarz, 1978).

Figure 2: Average misclassification errors on 1000 runs for different classification methods, increasing contamination rate.

4 Simulation study

In this Section, we present a simulation study that compares performances of several model-based classification methods in dealing with noisy data at different contamination rates, considering noise both on response and exploratory variables.

4.1 Experimental Setup

We consider a data generating process given by a mixture of components of bivariate normal distributions, according to the following parameters:

observations were generated from the model, randomly assigning to the labelled set and to the unlabelled set. The labelled set was subsequently adulterated with contamination rate (ranging from to ), wrongly assigning of the third group units to the first class and adding randomly labelled points generated from a Uniform distribution on the square with vertices . The contamination is therefore twofold, involving jointly label switching and outliers. Examples of labelled datasets with different contamination rates are reported in Figure 1. Performances of 6 model-based classification methods are considered:

EDDA 0.01 0.03 0.06 0.092 0.113 0.129
(0.005) (0.026) (0.049) (0.06) (0.059) (0.059)
UPCLASS 0.008 0.027 0.073 0.106 0.129 0.149
(0.004) (0.04) (0.076) (0.081) (0.076) (0.065)
RMDA 0.013 0.031 0.044 0.053 0.061 0.07
(0.021) (0.038) (0.039) (0.043) (0.043) (0.048)
RLDA 0.033 0.032 0.032 0.033 0.032 0.032
(0.013) (0.013) (0.013) (0.013) (0.013) (0.013)
REDDA 0.011 0.011 0.01 0.01 0.01 0.015
(0.005) (0.005) (0.005) (0.005) (0.005) (0.01)
RUPCLASS 0.008 0.008 0.008 0.008 0.008 0.009
(0.004) (0.004) (0.004) (0.004) (0.004) (0.006)
Table 2: Average misclassification errors on 1000 runs, varying method and contamination rate. Standard errors are reported in parenthesis.
  • EDDA: Eigenvalue Decomposition Discriminant Analysis (Bensmail and Celeux, 1996)

  • UPCLASS: Updating Classification Rules (Dean et al., 2006)

  • RMDA: Robust Mixture Discriminant Analysis (Bouveyron and Girard, 2009)

  • RLDA: Robust Linear Discriminant Analysis (Hawkins and McLachlan, 1997)

  • REDDA: Robust Eigenvalue Decomposition Discriminant Analysis. This is the supervised version of the model described in Section 3, where only the labelled observations are used for robust parameter estimation, enforcing impartial trimming as in (9)

  • RUPCLASS: Robust Updating Classification Rules. The semi-supervised proposed method described in Section 3.

For each contamination rate, experiments have been repeated times. To make a fair performance comparison, a level of (REDDA and RUPCLASS) and (RUPCLASS) have been kept fixed throughout the simulation study. Nevertheless, exploratory tools such as Density-Based Silhouette plot (Menardi, 2011) and trimmed likelihood curves (García-Escudero et al., 2011) could be employed to validate and assess the choice of and . A more automatic approach, like the one introduced in Dotto et al. (2018), could also be adapted to our framework. This, however, goes beyond the scope of the present manuscript, it will nonetheless be addressed in the future. A value of was selected for the eigenvalue-ratio restriction in (8). Simulation study results are presented in the following subsections.

4.2 Classification Performance

Figure 3: Box plots of the simulated distributions of , estimator of (upper panel); , estimator for (central panel); , estimator for (bottom panel) for the different models, varying contamination rate.

Average misclassification errors for the different methods and for varying contamination rates are reported in Table 2 and in Figure 2. The error rate is computed on the unlabelled dataset and averaged over the simulations. As expected, the misclassification error is fairly equal to all methods when there is no contamination rate, with the only exception being RLDA: this is due to the implicit model assumption that , which is not the case in our simulated scenario. As the contamination rate increases, so does the error rate for the non-robust methods (EDDA and UPCLASS), whereas for RLDA and RMDA it has a lower increment rate. Nevertheless, such methods fail to jointly cope with both sources of adulteration, namely class and attribute noise. Our proposals REDDA and RUPCLASS, thanks to the trimming step enforced in the estimation process, have always higher correct classification rates, on average, at any adulteration level. Notice that, to compare results of robust and non-robust methods, also the trimmed observations were classified a-posteriori according to the Bayes rule, assigning them to the component having greater value of .

On average, the robust semi-supervised approach performs better than the supervised counterpart, due to the information incorporated from genuine unlabelled data in the estimation process. Interestingly, the same behavior is not reflected in the non-robust counterparts, where the detrimental effect of contaminated labelled units magnifies the bias of the UPCLASS method. Therefore, robust solutions are even more paramount when a semi-supervised approach is considered.

4.3 Parameter Estimation

Figure 3 reports the box plots of the simulated distributions over Monte Carlo repetitions for some parameters of the first mixture component, namely with reference to (upper panel), (central panel) and (bottom panel). The estimation of the mixing proportion and the first element of the mean vector remain fairly stable, with the only exception of UPCLASS, for which is on average overestimated when increasing contamination is considered. Clearly, the estimation of the variance covariance matrices is badly affected in most extreme scenarios, where their entries are inflated in order to accommodate more and more bad points. Again, our robust proposals are less affected by the harmful effect of adding anomalous observations, also in the most adulterated scenario.

5 Application to Midinfrared Spectroscopy of Irish Honey

The semi-supervised method introduced in Section 3 is employed in performing adulteration detection and classification in a food authenticity context: we consider the task of discriminating between pure and adulterated Irish Honey, where the training set itself contains unreliable samples.

5.1 Honey Samples

Honey is defined as “the natural sweet substance, produced by honeybees from the nectar of plants or from secretions of living parts of plants, or excretions of plant-sucking insects on the living parts of plants, which the bees collect, transform by combining with specific substances of their own, deposit, dehydrate, store and leave in honeycombs to ripen and mature” (Alimentarius, 2001). Being a relatively expensive commodity to produce and extremely variable in nature, honey is prone to adulteration for economic gain: in 2015 the European Commission organized an EU coordinated control plan to assess the prevalence on the market of honey adulterated with sugars and honeys mislabelled with regard to their botanical source or geographical origin. It is therefore of prime interest to employ robust analytical methods to protect food quality and uncover its illegal adulteration.

We consider here a dataset of midinfrared spectroscopic measurements of 530 Irish honey samples. Midinfrared spectroscopy is a fast, non-invasive method for examining substances that does not require any sample preparation, it is therefore an effective procedure for collecting data to be subsequently used in food authenticity studies (Downey, 1996). The spectra measurements lie in the wavelength range of and , recorded at intervals of , with a total of 285 absorbance values. The dataset contains 290 Pure Honey observations, while the rest of the samples are honey diluted with adulterant solutions: 120 with Dextrose Syrup and 120 with Beet Sucrose, respectively. Kelly et al. (2006) gives a thorough explanation of the adulteration process. The aim of the study is to discriminate pure honey from the adulterated samples, when varying sample size of the labelled set whilst including a percentage of wrongly labelled units. Such a scenario is plausible to be encountered in real situations, since in a context in which the final purpose is to detect potential adulterated samples it may happen that the learning data is itself not fully reliable. An example of the data structure is reported in Figure 4.

5.2 Robust Dimensional Reduction

Prior to perform classification and adulteration detection, a preprocessing step is needed due to the high-dimensional nature of the considered dataset ( variables). To do so, we robustly estimate a factor analysis model, retaining a set of factors, , to be subsequently employed with the Robust Updating Classification Rules. Formally, for each Honey sample , we postulate a factor model of the form:

Figure 4: Midinfrared spectra for pure and contaminated honey, Irish Honey data.

where is a mean vector, is a matrix of factor loadings, are the unobserved factors, assumed to be realizations of a -variate standard normal and the errors are independent realizations of , with a diagonal matrix. In such a way, the observed variables are assumed independent given the factors. For a general review on factor analysis, see for example Chapter 9 in (Mardia et al., 1979). Parameters in (18) are estimated employing a robust procedure based on trimming and constraints (García-Escudero et al., 2016), yielding dimensionality reduction at the same time. Given the robustly estimated parameters, the latent traits are computed using the regression method (Thomson, 1939):


The estimated factors scores will be used for the classification task reported in the upcoming Section. For the considered dataset, after a graphical exploration of Cattell’s scree plot for the correlation matrix robustly estimated via MCD (Rousseeuw and Driessen, 1999), reported in Figure 5, we deem sufficient to set the number of latent factors equal to . Parameters were estimated setting a trimming level and .

Figure 5: Cattell’s scree plot (Cattell, 1966) for the first 50 eigenvalues of the robustly estimated correlation matrix, Irish Honey data. Green solid dots denote eigenvalues bigger than 1.

5.3 Classification Performance

After having performed robust dimensional reduction, the method described in Section 3 has been employed for discriminating between pure and adulterated honey samples. To do so, we divided the available data into a training (labelled) sample and a validation (unlabelled) sample. We investigated the effect of having different sample sizes in the labelled set, both in terms of classification accuracy and adulteration detection. Particularly, 3 proportions have been considered: - , - and - for splitting data into training and validation set, respectively, within each group. For each split, of the Beet Sucrose adulterated samples were incorrectly labelled as Pure Honey in the training set, adding class noise in the discrimination task. The trimming levels and were set equal to and , respectively. Table 3 summarizes the experimental results employing the proposed robust methodology, in its supervised and semi-supervised variants. As expected, the semi-supervised approach performs better in terms of classification rate, when the labelled sample size is small. Careful investigation has been dedicated to measuring the ability of the proposed methodology in correctly determining (i.e., trimming) the of incorrectly labelled samples, that is, units adulterated with Beet Sucrose and erroneously labelled as Pure Honey: % Correctly Trimmed indicates the class noise percentage correctly detected by the impartial trimming. For the recognized class noise, % Correctly Identified indicates the percentage of units properly a-posteriori assigned to the Beet Sucrose group. VEV and VVV models have been almost always chosen in each scenario: model selection was performed through the Robust criteria defined in Section 3.4. Results in Table 3 show that the proposed methodology is effective not only for accurately robustifying the parameter estimates, but also for efficiently detecting observations affected by class noise, firstly by trimming and subsequently by assigning them to the correct class they belong.

50% Tr - 50% Te Error Rate 0.038 0.04
(0.014) (0.014)
% Correctly Trimmed 0.993 0.997
(0.047) (0.024)
% Correctly Identified 1 1
(0) (0)
25% Tr - 75% Te Error Rate 0.054 0.053
(0.016) (0.024)
% Correctly Trimmed 0.8 0.993
(0.252) (0.047)
% Correctly Identified 0.97 1
(0.157) (0)
10% Tr - 90% Te Error Rate 0.101 0.08
(0.048) (0.042)
% Correctly Trimmed 0.48 0.9
(0.319) (0.247)
% Correctly Identified 0.73 0.96
(0.443) (0.198)
Table 3: Misclassification rates in the unlabelled set, % of wrongly labelled samples correctly trimmed in the labelled set and % of those correctly trimmed observations properly a-posteriori assigned to the Beet Sucrose group. Average values for 50 random splits in training and validation (3 proportions are considered), standard deviations reported in parentheses.

6 Concluding Remarks

In this paper we have proposed a robust modification to a family of semi-supervised patterned models, for performing classification in presence of both class and attribute noise.

We have shown that our methodology effectively addresses the issues generated by these two noise types, by identifying wrongly labelled units (noise in the response variable) and corrupted attributes in units (noise in the explanatory variables). Robust parameter estimates can therefore be obtained by excluding the noisy observations from the estimation procedure, both in the training set, and in the test set. Our proposal has been based on incorporating impartial trimming and eigenvalue-ratio constraints in previous semi-supervised methods. We have adapted the trimming procedure to the two different frameworks, i.e., for the labelled units and the unlabelled ones. After completing the robust estimation process, trimmed observations can be classified as well, by the usual Bayes rule. This final step allows the researcher to detect whether one observation is indeed extreme in terms of its attributes or it has been wrongly assigned to a different class. Such feature seems particularly desirable in food authenticity applications, where, due to imprecise readings and fraudulent units, it is likely to have label noise also within the labelled set. Some simulations, and a study on real data from pure and adulterated Honey samples, have shown the effectiveness of our proposal.

As an open point for further research, an automatic procedure for selecting reasonable values for the labelled and unlabelled trimming levels, along the lines of Dotto et al. (2018), is under study. Additionally, a robust wrapper variable selection for dealing with high-dimensional problems could be useful for further enhancing the discriminating power of the proposed methodology.


The authors are very grateful to Agustin Mayo-Iscar and Luis Angel García Escudero for both stimulating discussion and advices on how to enforce the eigenvalue-ratio constraints under the different patterned models. Andrea Cappozzo deeply thanks Michael Fop for his endless patience and guidance in helping him with methodological and computational issues encountered during the draft of the present manuscript.


This final Section presents feasible and computationally efficient algorithms for enforcing the eigenvalue-ratio constraint according to the different patterned models in Table 1. At the th iteration of the M step, the goal is to update the estimates for the variance-covariance matrices , such that,


where indicates the diagonal entries of matrix . Denote with the estimates for the variance covariance matrices obtained following Bensmail and Celeux (1996) without enforcing the eigenvalues-ratio restriction in (20). Lastly, denote with the matrix of eigenvalues for , with diagonal entries , .

Constrained maximization for VII, VVI and VVV models

  1. Compute applying the optimal truncation operator defined in Fritz et al. (2013) to , under condition (20)

  2. Set , ,

Constrained maximization for VVE model

  1. Compute applying the optimal truncation operator defined in Fritz et al. (2013) to , under condition (20)

  2. Given , compute the common principal components via, for example, a majorization-minimization (MM) algorithm (Browne and McNicholas, 2014)

  3. Set , ,

Constrained maximization for EVI, EVV models

  1. Compute applying the optimal truncation operator defined in Fritz et al. (2013) to , under condition (20)

  2. Compute constraining such that . That is, constraining to be equal across groups (Maronna and Jacovkis, 1974; Gallegos, 2002). Details are given in Section 3.2 of Fritz et al. (2012)

  3. Iterate until (20) is satisfied

  4. Set , ,

Constrained maximization for EVE model

  1. Compute applying the optimal truncation operator defined in Fritz et al. (2013) to , under condition (20)

  2. Compute constraining such that . Details are given in Section 3.2 of Fritz et al. (2012)

  3. Iterate until (20) is satisfied

  4. Given , compute the common principal components via, for example, a majorization-minimization (MM) algorithm (Browne and McNicholas, 2014)

  5. Set , ,

Constrained maximization for VEI, VEV models

  1. Set

  2. Set ,

  3. Compute applying the optimal truncation operator defined in Fritz et al. (2013) to , under condition (20)

  4. Compute

  5. Compute

  6. Set

  7. Iterate until (20) is satisfied

  8. Set , ,

Constrained maximization for VEE model

  1. Set

  2. Set ,

  3. Compute applying the optimal truncation operator defined in Fritz et al. (2013) to , under condition (20)

  4. Compute

  5. Compute

  6. Set

  7. Iterate until (20) is satisfied

  8. Considering the spectral decomposition for , set , ,


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