 Methodology article
 Open Access
 Published:
Supervised Regularized Canonical Correlation Analysis: integrating histologic and proteomic measurements for predicting biochemical recurrence following prostate surgery
BMC Bioinformatics volume 12, Article number: 483 (2011)
Abstract
Background
Multimodal data, especially imaging and nonimaging data, is being routinely acquired in the context of disease diagnostics; however, computational challenges have limited the ability to quantitatively integrate imaging and nonimaging data channels with different dimensionalities and scales. To the best of our knowledge relatively few attempts have been made to quantitatively fuse such data to construct classifiers and none have attempted to quantitatively combine histology (imaging) and proteomic (nonimaging) measurements for making diagnostic and prognostic predictions. The objective of this work is to create a common subspace to simultaneously accommodate both the imaging and nonimaging data (and hence data corresponding to different scales and dimensionalities), called a metaspace. This metaspace can be used to build a metaclassifier that produces better classification results than a classifier that is based on a single modality alone. Canonical Correlation Analysis (CCA) and Regularized CCA (RCCA) are statistical techniques that extract correlations between two modes of data to construct a homogeneous, uniform representation of heterogeneous data channels. In this paper, we present a novel modification to CCA and RCCA, Supervised Regularized Canonical Correlation Analysis (SRCCA), that (1) enables the quantitative integration of data from multiple modalities using a feature selection scheme, (2) is regularized, and (3) is computationally cheap. We leverage this SRCCA framework towards the fusion of proteomic and histologic image signatures for identifying prostate cancer patients at the risk of 5 year biochemical recurrence following radical prostatectomy.
Results
A cohort of 19 grade, stage matched prostate cancer patients, all of whom had radical prostatectomy, including 10 of whom had biochemical recurrence within 5 years of surgery and 9 of whom did not, were considered in this study. The aim was to construct a lower fused dimensional metaspace comprising both the histological and proteomic measurements obtained from the site of the dominant nodule on the surgical specimen. In conjunction with SRCCA, a random forest classifier was able to identify prostate cancer patients, who developed biochemical recurrence within 5 years, with a maximum classification accuracy of 93%.
Conclusions
The classifier performance in the SRCCA space was found to be statistically significantly higher compared to the fused data representations obtained, not only from CCA and RCCA, but also two other statistical techniques called Principal Component Analysis and Partial Least Squares Regression. These results suggest that SRCCA is a computationally efficient and a highly accurate scheme for representing multimodal (histologic and proteomic) data in a metaspace and that it could be used to construct fused biomarkers for predicting disease recurrence and prognosis.
Background
With the plentitude of multiscale, multimodal, disease pertinent data being routinely acquired for diseases such as breast and prostate cancer, there is an emerging need for powerful data fusion (DF) methods to integrate the multiple orthogonal data streams for the purpose of building diagnostic and prognostic metaclassifiers for disease characterization [1]. Combining data derived from multiple sources has the potential to significantly increase classification performance relative to performance trained on any one modality alone [2]. A major limitation in constructing integrated metaclassifiers that can leverage imaging (histology, MRI) and nonimaging (proteomics, genomics) data streams is having to deal with data representations spread across different scales and dimensionalities [3].
For instance, consider two different data streams F_{ A }(x) and F_{ B }(x) describing the same object x. If F_{ A } (x) and F_{ B }(x) correspond to the same scale or resolution and also have the same dimensionality, then one can envision, concatenating the two data vectors into a single unified vector [F_{ A }(x), F_{ B }(x)] which could then be used to train a classifier. However when F_{ A }(x) and F_{ B }(x) correspond to different scales, resolutions, and dimensionalities, it is not immediately obvious as to how one would go about combining the different types of measurements to build integrated classifiers to make predictions about the class label of x. For instance, directly aggregating data from very different sources without accounting for differences in the number of features and relative scaling, can not only lead to the curse of dimensionality (too many features and not enough corresponding samples [4]), but can lead to classifier bias towards the modality with more attributes. A possible solution is to first project the data streams into a space where the scale and dimensionality differences are removed; a metaspace allowing for a homogeneous, fused, multimodal data representation.
DF methods try to overcome these obstacles by creating such a metaspace, on which a proper metaclassifier can be constructed. Methods leveraging embedding techniques have been proposed to try and fuse such heterogeneous data for the purpose of classification and prediction [2, 3, 5–7]. However, all of these DF techniques have their own weaknesses in creating an appropriate representation space that can simultaneously accommodate multiple imaging and nonimaging modalities. Generalized Embedding Concatenation [5] is a DF scheme that relies on dimensionality reduction (DR) methods to first eliminate the differences in scales and dimensionalities between the modalities before fusing them. However, these DR methods face the risk of extracting noisy features which degrade the metaspace [8]. Other variants of the embedding fusion idea, including Consensus embedding [6] and Boosted embedding [3] have yielded promising results, but come at a high computational cost. Consensus embedding attempts to combine multiple low dimensional data projections via a majority voting scheme while the Boosted embedding scheme leverages the Adaboost classifier [9] to combine multiple weak embeddings. In the case of weighted multikernel embedding using graph embedding [7] and support vector machine classifiers [2], insufficient training data can lead to overfitting and inaccurate weights to the various kernels, which can lower the performance of the metaclassifier [10].
CCA is a statistical DF technique that extracts linear correlations, by using crosscovariance matrices, between 2 data sources, X and Y. It capitalizes on the knowledge that the different modalities represent different sets of descriptors for characterizing the same object. For this reason, the mutual information that is most correlated between the two modalities will provide the most meaningful transformation into a metaspace. In recent years, CCA has been used to fuse heterogeneous data such as pixel values of images and the text attached between these images [11], assets and liabilities in banks [12], and audio and face images of speakers [13].
Regularized CCA (RCCA) is an improved version of CCA which in the presence of insufficient training data prevents overfitting by using a ridge regression optimization scheme [14]. Denote p and q as the number of features in X and Y, and n as the sample size. When n < < p or n < < q, the features in X and Y tend to be highly collinear. This leads to illconditioned matrices C_{ xx } and C_{ yy }, which denote the covariance matrix of X with itself and Y with itself, such that their inverses are no longer reliable resulting in an invalid computation of CCA and an unreliable metaspace [15]. The condition placed on the data to guarantee that C_{ xx } and C_{ yy } will be invertible is n ≥ p + q + 1 [16]. However, that condition is usually not met in the bioinformatics domain, where samples (n) are usually limited, and modern technology has enabled very high dimensional data streams to be routinely acquired resulting in very high dimensional feature sets (p and q). This creates a need for regularization, which works by adding small positive quantities to the diagonals of C_{ xx } and C_{ yy } to guarantee their invertibility [17]. RCCA has been used to study expressions of genes measured in liver cells and compare them with concentrations of hepatic fatty acids in mice [18]. However, the regularization process required by RCCA is computationally very expensive. Both CCA and RCCA also fail to take complete advantage of class label information, when available [19].
In this paper, we present a novel efficient Supervised Regularized Canonical Correlation Analysis (SRCCA) DF algorithm that is able to incorporate a supervised feature selection scheme to perform regularization. Mainly, it makes better use of labeled information that in turn allows for significantly better stratification of the data in the metaspace. While SRCCA is more expensive than the overfittingprone CCA, it provides the needed regularization while also being computationally cheaper than RCCA. SRCCA first produces an embedding of the most correlated data in both modalities via a low dimensional metaspace. This representation is then used in conjunction with a classifier (KNearest Neighbor [20] and Random Forest [21] are used in this study) to create a highly accurate metaclassifier.
Along with CCA and RCCA, SRCCA is compared with 2 other low dimensional data representation techniques: Principal Component Analysis (PCA) and Partial Least Squares Regression (PLSR). PCA [22] is a linear DR method that reduces high dimensional data to dominant orthogonal eigenvectors that try to represent the maximal amount of variance in the data. PLSR [23] is a DR method that uses one modality as a set of predictors to try to predict the other modality. Tiwari et al. [24] employed PCA in conjunction with a wavelet based representation of different MRI protocols to build a fused classifier to detect prostate cancer in vivo. PLSR has been used with heterogeneous multivariate signaling data collected from HT29 human colon carcinoma cells stimulated to undergo programmed cell death to uncover aspects of biological cuesignalresponse systems [25].
In this work, we apply SRCCA to the problem of predicting biochemical recurrence in prostate cancer (CaP) patients, following radical prostatectomy, by fusing histologic imaging and proteomic signatures. Biochemical recurrence is commonly defined as a detectable elevation of Prostate Specific Antigen (PSA), a key biomarker for CaP [26–28]. However, the nonspecificity of PSA leads to overtreatment of CaP, resulting in many unnecessary treatments, which are both stressful and costly [29–33]. Even the most widely used prognostic markers such as pathologist assigned Gleason grade [34], which attempts to capture the morphometric and architectural appearance of CaP on histopathology, has been found to be a less than perfect predictor of biochemical recurrence [35]. Additionally, Gleason grade has been found to be subject to inter, and intraobserver variability [36–38]. While some researchers have proposed quantitative, computerized image analysis approaches [1, 39, 40] for modeling and predicting Gleason grade (a number that goes from 1 to 5 based on morphologic appearance of CaP on histopathology), it is still not clear that an accurate, reproducible grade predictor from histology will also be accurate in predicting biochemical recurrence and long term patient outcome [41].
Recent studies have shown that proteomic markers can be used to predict aggressive CaP [42, 43]. Techniques such as mass spectrometry hold promise in their ability to identify protein expression profiles that might be able to distinguish more aggressive from less aggressive CaP and identify candidates for biochemical recurrence [44–46]. However, more and more, it is becoming apparent that a single prognostic marker may not possess sufficient discriminability to predict patient outcome which suggests that the solution might lie in an integrated fusion of multiple markers [47]. This then begs the question as to what approaches need to be leveraged to quantitatively fuse imaging and nonimaging measurements to build an integrated prognostic marker for CaP recurrence. The overarching goal of this study is to leverage SRCCA to construct a fused quantitative histologic, proteomic marker, and a subsequent metaclassifier, for predicting 5 year biochemical recurrence in CaP patients following surgery.
Our main contributions in this paper are:

A novel data fusion algorithm, SRCCA, that builds an accurate metaspace representation that can simultaneously represent and accommodate two heterogeneous imaging and nonimaging modalities.

Leveraging SRCCA to build a metaclassifier to predict risk of 5 year biochemical recurrence in prostate cancer patients following radical prostatectomy by integrating histological image and proteomic features.
The organization of the rest of the paper is as follows: In the methods section, we first review the 4 statistical methods, PCA, PLSR, CCA and RCCA. Next, we introduce our novel algorithm, Supervised Regularized Canonical Correlation Analysis (SRCCA). We then discuss the DF algorithm for metaspace creation and the computational complexities for CCA, RCCA and SRCCA. In the Experimental Design section, we briefly discuss the prostate cancer dataset considered in this study and the subsequent proteomic and histologic feature extraction schemes before moving on to the experiments performed on the dataset where we try to determine the ability of PCA, PLSR, CCA, RCCA and SRCCA to identify patients at risk for biochemical recurrence following surgery. The results are discussed in the subsequent section and the concluding remarks are presented at the end of the paper.
Methods
Review of PCA and PLSR
Principal Component Analysis (PCA) and Partial Least Squares Regression (PLSR) are common statistical methods used to analyze multimodal data and they are briefly discussed in the following sections. However, further information, explaining how these two methods can be viewed as special cases of the generalized eigenproblem, can be found in [48].
Principal Component Analysis (PCA)
PCA [22] constructs a low dimensional subspace of the data by finding a series of linear orthogonal bases called principal components. Each component seeks to explain the maximal amount of variance in the dataset. Denote two multidimensional variables, X ∈ ℝ^{n × p}and Y ∈ ℝ^{n×q}, where p and q are the number of features in X and Y and n the number of overall samples. PCA is usually performed on the data matrix, Z ∈ ℝ^{n×(p+q)}, obtained by concatenating the individual modalities such that: Z = [X Y] [24]. $\stackrel{\u0304}{Z}\in {\mathbb{R}}^{n\phantom{\rule{2.77695pt}{0ex}}\times \phantom{\rule{2.77695pt}{0ex}}\left(p+q\right)}$ is then obtained by subtracting the means of all features for a certain sample from its original feature value in Z so that the resultant $\stackrel{\u0304}{Z}$ has rows with a 0 mean. $\stackrel{\u0304}{Z}$ is further broken using singular value decomposition into [22]:
where E ∈ ℝ^{n×n}is a diagonal matrix containing the eigenvalues of the eigenvectors which are stored in U ∈ ℝ^{p×p}, and V^{T}∈ ℝ^{m×n}. The eigenvalues stored in E explain how much variance of the original $\stackrel{\u0304}{Z}$ is stored in the corresponding eigenvector, or principal component. Using these eigenvalues as a rank, the top d embedding components can be chosen to best represent the original data in a lower dimensional subspace.
Partial Least Squares Regression(PLSR)
PLSR [49] is a statistical technique that generalizes PCA and multiple regression. The general underlying model behind PLSR is [23]:
where T ∈ ℝ^{n×l}is a score matrix, P ∈ ℝ^{p×l}and C ∈ ℝ^{q×l}are loading matrices for X and Y, and E ∈ ℝ^{n×p}and F ∈ ℝ^{n×p}are the error terms. PLSR is an iterative process and works by continually approximating, and improving the approximation of the matrices T, P and C [50].
Review of CCA and RCCA
Canonical Correlation Analysis (CCA)
CCA [51] is a way of using crosscovariance matrices to obtain a linear relationship between the two multidimensional variables, X ∈ ℝ^{n×p}and Y ∈ ℝ^{n×q}. CCA obtains two directional vectors w_{ x } ∈ ℝ^{p×1}and w_{ y } ∈ ℝ^{q×1}such that Xw_{ x } and Yw_{ y } will be maximally correlated. It is defined as the optimization problem [11]:
where C_{ xy } ∈ ℝ^{p×q}is the covariance matrix of the matrices X and Y, C_{ xx } ∈ ℝ^{p×p}is the covariance matrix of the matrix X with itself and C_{ yy } ∈ ℝ^{q × q}is the covariance matrix of the matrix Y with itself. The solution to CCA reduces to the solution of the following two generalized eigenvalue problems [52]:
where λ is the generalized eigenvalue representing the canonical correlation, and w_{ x } and w_{ y } are the corresponding generalized eigenvectors. CCA can further produce exactly min{p, q) orthogonal embedding components (sets of w_{ x }X and w_{ y }Y) which can be sorted in order of decreasing correlation, λ.
Regularized Canonical Correlation Analysis (RCCA)
RCCA [53, 54] corrects for noise in X and Y by first assuming that X and Y are contaminated with noise, N_{ x } ∈ ℝ^{n×p}and N_{ Y } ∈ ℝ^{n×q}. We assume that these noise vectors in the p and q columns of N_{ X } and N_{ Y }, respectively, are gaussian, independent and identically distributed. For this reason, all combinations of the covariances of the p columns of N_{ X } and q columns of N_{ Y } will be 0 except the covariance of a particular column vector with itself. This variance of each column of N_{ X } and N_{ Y } is labeled λ_{ x } and λ_{ y } and these labels are called the regularization parameters. The matrix C_{ xy } will not be affected but the matrices C_{ xx } and C_{ yy } become C_{ xx } + λ_{ x } I_{ x } and C_{ yy } + λ_{ x } I_{ x }. The solution to RCCA now becomes the solution to these generalized eigenvalue problems [52]:
The regularization parameters next have to be chosen. For i ∈ {1, 2, . . . , n}, let ${w}_{x}^{i}$ and ${w}_{y}^{i}$ denote the weights calculated from RCCA when samples X_{ i } and Y_{ i } are removed. λ_{ x } and λ_{ y } are varied in a certain range θ_{1} ≤ λ_{ x }, λ_{ y } ≤ θ_{2} and chosen via a grid search [55] optimization of the following cost function [18]:
where corr (·, ·) refers to the Pearson's correlation coefficient [56]. The above cost function essentially measures the change in the produced ${w}_{x}^{i}$ and ${w}_{y}^{i}$ when a sample i is omitted and seeks the optimal λ_{ x } and λ_{ y } where this change is minimized. λ_{ x } and λ_{ y } are chosen using the embedding component with the highest λ and then adjusted for the remaining dimensions [18].
Extending RCCA to SRCCA
Supervised Regularized Canonical Correlation Analysis (SRCCA) chooses λ_{ x } and λ_{ y } using a supervised feature selection method (ttest, Wilcoxon Rank Sum Test and Wilks Lambda Test are used in this study). Denote ${\mathbb{W}}_{\mathsf{\text{1}}}$ and ${\mathbb{W}}_{2}$ as class 1 and class 2 and μ_{1} and μ_{2}, ${\sigma}_{1}^{2}$ and ${\sigma}_{2}^{2}$, n_{1} and n_{2} as the means, variances, and sample sizes of ${\mathbb{W}}_{\mathsf{\text{1}}}$ and ${\mathbb{W}}_{2}$. The data in the metaspace, Xw_{ x } or Yw_{ y }, can be split using its labels into the n_{1} samples that belong to ${\mathbb{W}}_{\mathsf{\text{1}}}$ and the n_{2} samples that belong to class ${\mathbb{W}}_{2}$, where n_{1} + n_{2} = n. These two partitions can then be used to calculate the discrimination level between the samples of the two classes in the metaspace representation. In this study, we implement RCCA with the ttest (SRCCA_{ TT }), the Wilcoxon Rank Sum Test (SRCCA_{ WRST }) and the Wilks Lambda Test (SRCCA_{ WLT }) to try to choose more appropriate regularization parameters, λ_{ x } and λ_{ y }, that can more successfully stratify the samples in the metaspace compared to the parameters chosen by RCCA. Similar to RCCA, for SRCCA, λ_{ x } and λ_{ y } are chosen using the embedding component with the most discriminatory score as chosen by the feature selection schemes below and then adjusted for the remaining dimensions.
SRCCA_{TT}
The ttest [57] is a parametric test that assumes the distributions of the two samples are normal and tests whether these distributions have the same means. The tscore, which measures the number of standard deviations the two means of n_{1} samples of ${\mathbb{W}}_{\mathsf{\text{1}}}$ and n_{2} samples of ${\mathbb{W}}_{2}$ are away from each other, is maximized using a grid search algorithm as:
SRCCA_{WRST}
Wilcoxon Rank Sum Test [58] sorts both the samples in order from lowest value to highest value. It then uses their respective ranks within the population to calculate the discriminatory score:
where b_{ i } represents the rank of the sample $i\phantom{\rule{0.3em}{0ex}}\in \phantom{\rule{0.3em}{0ex}}{\mathbb{W}}_{2}$ with respect to the rest of the samples.
SRCCA_{W LT}
In an ideal metaspace representation, samples from each class will be grouped together while the samples from different classes will be grouped separately. The WLT [59] capitalizes on this knowledge and calculates the ratio of within class variance of both samples to the total variance of both samples combined. Wilks Lambda (Λ) is minimized using a grid search algorithm as:
Data Fusion in the context of CCA, RCCA and SRCCA
DF is performed as described in Foster et al. [60]. When the Xw_{ x } and Yw_{ y } are maximally correlated, each modality represents similar information, and thus either Xw_{ x } or Yw_{ y } can be used to represent the original two modalities in the metaspace. Moreover, X and Y are both descriptors of the same object and thus, the most relevant information is the data that exists and is correlated in both modalities. Thus, a high correlation of Xw_{ x } and Yw_{ y } is indicative that meaningful data, measuring the object of interest, is being added to the metaspace.
In order of decreasing λ, the top d embedding components, up to φ = min{p, q} can be chosen to represent the two modalities in a metaspace. However, the lower embedding components will have a lower λ, and thus a lower correlation between Xw_{ x } and Yw_{ y } which might imply that nonrelevant data is being added to the metaspace. To avoid this issue, a threshold, λ_{0}, can be selected such that only embedding components with λ ≥ λ_{0} will be included in the metaspace.
Computational Complexity
Given φ = min{p, q}, CCA has a computational complexity of φ! (based on the source code in [61]). The regularization algorithm requires a grid search process for each ordered pair (λ_{ x }, λ_{ y }). Assume v potential λ_{ x } and λ_{ y } sampled evenly between θ_{1} and θ_{2}. RCCA requires a training/testing crossvalidation strategy, at each ordered pair (λ_{ x }, λ_{ y }), to find the optimal λ_{ x } and λ_{ y }. It will require CCA to be performed an order of n times at each of the v intervals leading to a complexity of vnφ!. SRCCA only requires a CCA factorization once at each of the v intervals leading to a complexity of vφ!.
The computational complexities for each of the CCA schemes are summarized in Table 1. Table 1 indicates that SRCCA is an order of n times faster compared to RCCA. However, SRCCA is also more complex compared to CCA and will have a longer execution time.
Experimental Design
Data Description
A total of 19 prostate cancer patients at the Hospital at the University of Pennsylvania were considered for this study. All patient identifiers are stripped from the data at the time of acquisition. The data was deemed to be exempt for review by the internal review board at Rutgers University and the protocol was approved by the University of Pennsylvania internal review board. Hence, the data was deemed eligible for use in this study. All of these patients had been found to have prostate cancer on needle core biopsy and subsequently underwent radical prostatectomy. 10 of these patients had biochemical recurrence within 5 years following surgery (BR) and the other 9 did not (NO BR). The 19 patient studies were randomly chosen from a larger cohort of 110 patient studies at the University of Pennsylvania all of whom had been stage and grade matched (Gleason score of 6 or 7) and had undergone gland resection. Of these 110 cases, 55 had experienced biochemical recurrence within 5 years while the other 55 had not. The cost of the mass spectrometry to acquire the proteomic data limited this study to only 19 patient samples. Following gland resection, the gland was sectioned into a series of histological slices with a meat cutter. For each of the 19 patient studies, a representative histology section on which the dominant tumor nodule was observable was identified. Mass Spectrometry was performed at this site to yield a protein expression vector. The representative histologic sections were then digitized at 40 × magnification using a whole slide digital scanner.
In the next two sections, we briefly describe the construction of the proteomic and histologic feature spaces. Subsequently we describe the strategy for combination of quantitative image descriptors from the tumor site on the histological prostatectomy specimen and the corresponding proteomic measurements obtained from the same tumor site, via mass spectrometry. The resultant metaclassifier, constructed in the fused metaspace, is then used to distinguish the patients at 5 year risk of biochemical recurrence following radical prostatectomy from those who are not.
Proteomic Feature Selection
Prostate slides were deparaffinized, and rehydrated essentially as described in [62]. Tumor areas previously defined on a serial H&E section were collected by needle dissection, and formalin crosslinks were removed by heating at 99°C. The FASP (FilterAided Sample Preparation) method [63] was then used for buffer exchange and tryptic digest. After peptide purification on C18 StageTips [64] samples were analyzed using nanoflow C18 reverse phase liquid chromatography/tandem mass spectrometry (nLCMS/MS) on an LTQ Orbitrap mass spectrometer. A top5 datadependent methodology was used for MS/MS acquisition, and data files were processed using the Rosetta Elucidator proteomics package, which is a labelfree quantitation package that uses extracted ion chromatograms to calculate protein abundance rather than peptide counts. A high dimensional feature vector was obtained, denoted ϕ^{P}∈ ℝ^{19 × 953}, characterizing each patient's protein expression profile following surgery. This data underwent quantile normalization, log(2) transformation, and mean and variance normalization on a perprotein basis.
Quantitative Histologic Feature Extraction
In prostate wholemount histology, denoted ϕ^{H}∈ ℝ^{19 × 151} (Figure 1 (a), (f)), the objects of interest are the glands (shown in Figure 1 (b), (g)), whose shape and arrangement are highly correlated with cancer progression [1, 39, 65, 66]. We briefly describe this process below. Prior to extracting image features, we employ an automatic regiongrowing gland segmentation algorithm presented by Monaco et al. [67]. The boundaries of the interior gland lumen and the centroids of each gland, allow for extraction of 1) morphological and 2) architectural features from histology as described briefly below. More extensive details on these methods are in our other publications [5, 39, 68].
Glandular Morphology
The set of 100 morphological features [1], (denoted ϕ^{M}∈ ℝ^{19 × 100}), of attributes, consists of the average, median, standard deviation, and min/max ratio for features such as gland area, maximum area, area ratio, and estimated boundary length (See Table 2).
Architectural Feature Extraction
51 architectural image features, which have been shown to be predictors of cancer [69], (denoted ϕ^{A}∈ ℝ^{19 × 51}), were extracted in order to quantify the arrangement of glands present in the section (See Table 2). Voronoi diagrams, Delaunay Triangulation and Minimum Spanning Trees were constructed on the digital histologic image using the gland centroids as vertices, the gland centroids having previously been identified via the scheme in [68].
Fusing Proteomic, Histologic Features for Predicting Biochemical Recurrence in CaP Patients PostSurgery
Experiment 1  Comparing SRCCA with CCA and RCCA
We performed CCA, RCCA, and SRCCA on selected multimodal combinations, ϕ^{P}and ϕ^{J}, where J ∈ {M, A, H}. ϕ^{P}was reduced to 25 features as ranked by the ttest, with a pvalue cutoff of p = .05, using a leaveoneout validation strategy. For CCA, ϕ^{P}and ϕ^{J}were used as the two multidimensional variables, X and Y, as mentioned above in Section 2. For RCCA and SRCCA, ϕ^{P}and ϕ^{J}were used in a manner similar to CCA except they are tested with regularization parameters λ_{ x } and λ_{ y } evenly spaced from θ_{1} = .001 to θ_{2} = .2 with v = 200.
The top d = 3 embedding components (which were experimentally found to meet the criteria of λ_{0} = .99 for all SRCCA on all 3 multimodal combinations) were produced from CCA, RCCA, SRCCA_{ TT }, SRCCA_{ WRST }, and SRCCA_{ WLT }. The classification accuracies were determined with the classifiers KNearest Neighbor, denoted via ϕ^{KNN}[20], with K = 1, and Random Forest, denoted via ϕ^{RF}[21], with 50 Trees. Both these classifiers were used because of their high computational speed. Accuracies were determined using leaveoneout validation, which was implemented because of the small sample size. In this process, 18 samples were used for the initial feature pruning, determining the optimal regularization parameter and training the classifier while the remaining sample was used as the testing set for evaluating the classifier. This procedure was repeated till all the samples were used in the testing set.
Experiment 2  Comparing SRCCA with PCA and PLSR
In addition to the steps performed in Experiment 1, metaspaces were also produced with PCA and PLSR. ϕ^{P}and ϕ^{J}were concatenated and PCA was then performed on this new data matrix. For PLSR, a regression of ϕ^{J}on ϕ^{P}was performed.
Similarly, using the top d = 3 embedding components produced from PCA, PLSR, SRCCA_{ TT }, SRCCA_{ WRST }, and SRCCA_{ WLT }, the classification accuracies of ϕ^{KNN}, with K = 1, and ϕ^{RF}, with 50 Trees, were determined using leaveoneout validation.
Experiment 3  Comparing classifier accuracy for PCA, PLSR and CCA variants using metaspace representations
Using the 10 different values for d ∈ {1, 2, ..10}, and the 3 fusion schemes considered (ϕ^{P}, ϕ^{M}), (ϕ^{P}, ϕ^{A}), and (ϕ^{P}, ϕ^{H}), 30 different embeddings were obtained for PCA, PLSR, CCA, RCCA, SRCCA_{ TT }, SRCCA_{ WRST }, and SRCCA_{ WLT }. The maximum and median of these 30 different measurements for each classifier were calculated.
In addition, we denote as α_{1}(i), the classification accuracy obtained by the DF scheme i, where i ∈ {PCA, PLSR, CCA, RCCA} and α_{2}(j) as the accuracy obtained by the DF scheme i, where j ∈ {SRCCA_{ TT }, SRCCA_{ WRST }, SRCCA_{ WLT }}. A two paired student ttest was employed to identify whether there were statistically significant improvements in the 3 SRCCA variants by comparing the classification accuracies with the null hypothesis:
for all i ∈ {PCA, PLSR, CCA, RCCA} and for all j ∈ {SRCCA_{ TT }, SRCCA_{ WRST }, SRCCA_{ WLT }}.
Experiment 4  Computational consideration for RCCA and SRCCA
We measured the 3 individual single run completion times for RCCA and SRCCA to fuse (ϕ^{P}, ϕ^{M}), (ϕ^{P}, ϕ^{A}), and (ϕ^{P}, ϕ^{H}), with the null hypothesis:
These experiments were performed on a quadcore computer with a clock speed of 1.8 GHz, and the programs were written on MATLAB(R) platform.
Results and Discussion
Experiment 1
Across both classifiers for d = 3, the 3 SRCCA variants, SRCCA_{ TT }, SRCCA_{ WRST }, SRCCA_{ WLT }, had a combined median classification accuracy of 80% compared to 60% for CCA and 42% for RCCA. SRCCA also performed better in all 36 of 36 direct comparisons with CCA and RCCA (see Tables 3 and 4). The higher classification accuracy results indicate that SRCCA produces a metaspace, where the samples are more stratified, compared to CCA and RCCA. This also seems to indicate that the supervised scheme of choosing regularization parameters, by the 3 SRCCA variants, is a more appropriate scheme for classification purposes compared to the ridge regression scheme used by RCCA.
These results, which seem to suggest that SRCCA outperforms the other two CCA based approaches for this dataset, CCA and RCCA, are observable in the embedding plots of Figure 2, which show the metaspace produced by CCA, RCCA, SRCCA_{ TT }, SRCCA_{ WRST } and SRCCA_{ WLT } with d = 2 components. It may be seen that because CCA lacks regularization, the corresponding covariance matrices are singular and lack inverses. For this reason, in Figure 2 the embedding components are not orthogonal but are highly correlated to each other and yield the same information. RCCA overcomes this regularization problem but still does not produce the same level of discrimination between patient classes compared to the 3 variations of SRCCA. Note that SRCCA_{ TT }, SRCCA_{ WRST } and SRCCA_{ WLT } chose similar regularization parameters, λ_{ x } and λ_{ y }, and have similar embedding plots.
Experiment 2
We see that SRCCA_{ TT }, SRCCA_{ WRST }, SRCCA_{ WLT } are able to outperform PCA and PLSR in all 36 of 36 direct comparisons (see Tables 5 and 6). Even though, across both classifiers for d = 3, PCA and PLSR have median classification accuracies of 64% and 61%, which is higher than the accuracies for CCA and RCCA, it is still much lower than the 80% for SRCCA_{ TT }, SRCCA_{ WRST }, SRCCA_{ WLT }. These results also seem to indicate that SRCCA_{ TT }, SRCCA_{ WRST }, SRCCA_{ WLT } could also create a more appropriate metaspace than, not only CCA and RCCA, but also PCA and PLSR.
Experiment 3
In Tables 7 and 8 we see that the maximum and median ϕ^{KNN}and ϕ^{RF}of the 3 SRCCA variants for fusion of (ϕ^{I}, ϕ^{J}) were much higher than the corresponding values of PCA, PLSR, CCA or RCCA. We also see that SRCCA_{ WLT } attains a maximum classifier accuracy of 93.16% (see Table 7). In Tables 9 and 10, the 3 SRCCA variants are statistically significantly better than PCA, PLSR, CCA or RCCA even at the p = .001 level using either classifiers, ϕ^{KNN}or ϕ^{RF}. We further see that SRCCA_{ WLT } tends to marginally outperform SRCCA_{ TT } and SRCCA_{ WRST }. However given the small sample size it is difficult to draw any definitive conclusions about which of SRCCA_{ TT }, SRCCA_{ WRST }, or SRCCA_{ WLT } might be the better SRCCA variant.
In Figures 3 and 4, we see the classification accuracies of the 7 DF methods, PCA, PLSR, CCA, RCCA, SRCCA_{ TT }, SRCCA_{ WRST }, or SRCCA_{ WLT } over a range of d ∈ {1, 2, ..10} embedding components for the fusion (ϕ^{P}, ϕ^{H}). Importantly, we see that the SRCCA_{ TT }, SRCCA_{ WRST }, and SRCCA_{ WLT } all outperform PCA, PLSR, CCA and RCCA for a majority of the embedding dimensions, across both the ϕ^{KNN}and ϕ^{RF}classifiers.
Experiment 4
Figure 5 reveals that the completion time of SRCCA is significantly lower than the completion time of RCCA. Even though the differences in these times are visibly different, a pvalue of 1.9 × 10^{3} even with just 3 samples, indicates that SRCCA appears to be statistically significantly faster compared to RCCA.
Note that the canonical factorization stage is the most time consuming part of the of the algorithm. The Feature Selection stage computation, in comparison, is not as time consuming. SRCCA_{ TT }, SRCCA_{ WRST }, and SRCCA_{ WLT } (whose results are reported in Figure 5) all have similar execution times.
Conclusions
In this paper, we presented a novel data fusion (DF) algorithm called Supervised Regularized Canonical Correlation Analysis (SRCCA) that, unlike CCA and RCCA, is (1) able to fuse with a feature selection (FS) scheme, (2) regularized, and (3) computationally cheap. We demonstrate how SRCCA can be used for quantitative integration and representation of multiscale, multimodal imaging and nonimaging data. In this work we leveraged SRCCA for the purpose of constructing a fused quantitative histologicproteomic classifier for predicting which prostate cancer patients are at risk for 5 year biochemical recurrence following surgery. We have demonstrated that SRCCA is able to (1) produce a metaspace, where the samples are more stratified than the metaspace produced by CCA or RCCA, (2) better identify patients at the risk of biochemical recurrence compared to Principal Component Analysis (PCA), Partial Least Squares Regression (PLSR), CCA or RCCA, (3) perform regularization, all the while being statistically significantly faster compared to RCCA.
While the fused prognostic classifier for predicting biochemical recurrence in this work appears to be promising, we also acknowledge the limitations of this work: (1) As previously mentioned, the cost of mass spectrometry limited this study to only 19 datasets. By using a minimum sample size derivation model [70, 71], we were able to determine that our fused SRCCA classifier would yield an accuracy of 93%, more than 95% of the time if our dataset were expanded to 56 studies. We intend to evaluate our classifier on such a cohort in the future. (2) Ideally, a randomized cross validation strategy should have been employed for the training and evaluation of the classifier. Unfortunately, this was also limited by the size of the cohort. While both parametric and nonparametric feature selection strategies were employed in this work, the availability of a larger dataset for classification in conjunction with SRCCA would allow for employment of parametric selection strategies, assuming that the underlying distribution can be estimated. For small sample datasets, a nonparametric feature selection strategy might be more approrpriate. In future work, we also plan to apply SRCCA in the context of data fusion for other imaging and nonimaging datasets in the context of other problem domains and applications.
Abbreviations
 DF:

Data Fusion
 CCA:

Canonical Correlation Analysis
 RCCA:

Regularized Canonical Correlation Analysis
 SRCCA:

Supervised Regularized Canonical Correlation Analysis
 PCA:

Principal Component Analysis
 PLSR:

Partial Least Squares Regression
 DR:

Dimensional Reduction
 CaP:

Prostate Cancer
 PSA:

Prostate Specific Antigen
 MS:

Mass Spectrometry
 ϕ ^{KNN} :

KNearest Neighbor
 ϕ ^{RF} :

Random Forest.
References
 1.
Madabhushi A, Agner S, Basavanhally A, Doyle S, Lee G: Computeraided prognosis: Predicting patient and disease outcome via quantitative fusion of multiscale, multimodal data. CMIG 2011.
 2.
Lanckriet GRG, Deng M, Cristianini N, Jordan MI, Noble WS: Kernelbased data fusion and its application to protein function prediction in yeast. Proceedings of the Pacific Symposium on Biocomputing 2004, 300–311.
 3.
Tiwari P, Viswanath S, Lee G, Madabhush A: MultiModal Data Fusion Schemes for Integrated Classification of Imaging and Nonimaging Biomedical Data. ISBI 2011, 165–168.
 4.
Duda RO, Hart PE: Pattern Classification and Scene Analysis. John Wiley & Sons, New York; 1973.
 5.
Lee G, Monaco J, Doyle S, Masters S, Feldman M, Tomaszewski J, Madabhushi A: A knowledge representation framework for integration, classification of multiscale imaging and nonimaging data: Preliminary results in predicting prostate cancer recurrence by fusing mass spectrometry and histology. ISBI 2009, 77–80.
 6.
Viswanath S, Rosen M, Madabhushi A: A consensus embedding approach for segmentation of high resolution in vivo prostate magnetic resonance imagery. SPIE Med Imag 2008., 6915(1): 69150U 69150U
 7.
Tiwari P, Kurhanewicz J, Rosen M, Madabhushi A: Semi Supervised Multi Kernel (SeSMiK) Graph Embedding: Identifying Aggressive Prostate Cancer via Magnetic Resonance Imaging and Spectroscopy. MICCAI 2010, 6363: 666–673.
 8.
Wu Y, Chang EY, Chang KCC, Smith JR: Optimal Multimodal Fusion for Multimedia Data Analysis. ACM Conference on Multimedia 2004, 572–579.
 9.
Freund Y, Schapire RE: A decisiontheoretic generalization of online learning and an application to boosting. In Proceedings of the Second European Conference on Computational Learning Theory. London, UK: SpringerVerlag; 1995:23–37.
 10.
Lewis DP, Jebara T, Noble WS: Support vector machine learning from heterogeneous data: an empirical analysis using protein sequence and structure. Bioinformatics 2006, 22(22):2753–2760. 10.1093/bioinformatics/btl475
 11.
Hardoon DR, Szedmak S, ShaweTaylor J: Canonical correlation analysis: an overview with application to learning methods. Neural Comput 2004, 16(12):2639–2664. 10.1162/0899766042321814
 12.
Simonson DG, Stowe JD, Watson CJ: A Canonical Correlation Analysis of Commercial Bank Asset/Liability Structures. Journal of Financial and Quantitative Analysis 1983, 18(01):125–140. 10.2307/2330808
 13.
Chaudhuri K, Kakade SM, Livescu K, Sridharan K: MultiView Clustering via Canonical Correlation Analysis. Proceedings of the 26th Annual International Conference on Machine Learning 2009, 129–136.
 14.
Bie TD, Moor BD: On the Regularization of Canonical Correlation Analysis. ICA 2003 2003.
 15.
Gou Z, Fyfe C: A canonical correlation neural network for multicollinearity and functional data. Neural Networks 2004, 17(2):285–293. 10.1016/j.neunet.2003.07.002
 16.
Eaton ML, Perlman MD: The NonSingularity of Generalized Sample Covariance Matrices. The Annals of Statictics 1973, 1(4):710–717. 10.1214/aos/1176342465
 17.
Hoerl AE, Kennard RW: Ridge Regression: Biased Estimation for Nonorthogonal Problems. Technometrics 1970, 12: 55–67. 10.2307/1267351
 18.
Gonzalez I, Dejean S, Martin PGP, Baccini A: CCA: An R Package to Extend Canonical Correlation Analysis. Journal of Stat Software 2008, 23(12):1–14.
 19.
Kakade SM, Foster DP: MultiView Regression via Canonical Correlation Analysis. In Proceedings of Conference on Learning Theory 2007, 82–96.
 20.
Cover T, Hart P: Nearest neighbor pattern classification. Information Theory, IEEE Transactions on 1967, 13: 21–27.
 21.
Breiman L: Random Forests. Machine Learning 2001, 45: 5–32. 10.1023/A:1010933404324
 22.
Hotelling H: Analysis of a complex of statistical variables into principal components. Journal of Educational Psychology 1933, 24(7):498–520.
 23.
Wold S, Sjostrom M, Eriksson L: PLSregression: a basic tool of chemometrics. Chemometrics and Intelligent Laboratory Systems 2001, 58(2):109–130. 10.1016/S01697439(01)001551
 24.
Tiwari P, Kurhanewicz J, Viswanath S, Sridhar A, Madabhushi A: Multimodal Wavelet Embedding Representation for data Combination (MaWERiC): Integrating Magnetic Resonance Imaging and Spectroscopy for Prostate Cancer Detection. NMR in Biomedicine 2011, in press.
 25.
Janes KA, Kelly JR, Gaudet S, Albeck JG, Sorger PK, Lauffenburger DA: Cuesignalresponse analysis of TNFinduced apoptosis by partial least squares regression of dynamic multivariate data. Journal of computational biology a journal of computational molecular cell biology 2004, 11(4):544–561.
 26.
Pound CR, Partin AW, Eisenberger MA, Chan DW, Pearson JD, Walsh PC: Natural History of Progression After PSA Elevation Following Radical Prostatectomy. JAMA: The Journal of the American Medical Association 1999, 281(17):1591–1597. 10.1001/jama.281.17.1591
 27.
Roberts SG, Blute ML, Bergstralh EJ, Slezak JM, Zincke H: PSA doubling time as a predictor of clinical progression after biochemical failure following radical prostatectomy for prostate cancer. Mayo Clinic Proceedings 2001, 76(6):576–81. 10.4065/76.6.576
 28.
Pisansky TM, Kozelsky TF, Myers RP, Hillman DW, l Blute M, Buskirk SJ, Cheville JC, Ferrigni RG, Schild SE: Radiotherapy for Isolated Serum Prostate Specific Antigen Elevation After Prostatectomy For Prostate Cancer. The Journal of Urology 2000, 163(3):845–850. 10.1016/S00225347(05)678172
 29.
Chrouser K, Lieber M: Extended and saturation needle biopsy for the diagnosis of prostate cancer. Current Urology Reports 2004, 5: 226–230. 10.1007/s1193400400417
 30.
Welch H, Fisher E, Gottlieb D, Barry M: Detection of prostate cancer via biopsy in the medicareseer population during the PSA era. Journal of the National Cancer Institute 2007, 99: 1395–1400. 10.1093/jnci/djm119
 31.
Veenstra TD: Global and targeted quantitative proteomics for biomarker discovery. Journal of Chromatography B 2007, 847: 3–11. 10.1016/j.jchromb.2006.09.004
 32.
Chan DW, Sokoll LJ: Prostatespecific antigen: update 1997. Journal of the International Federation of Clinical Chemistry 1997, 9: 120–125.
 33.
Partin AW, Oesterling JE: The clinical usefulness of percent freePSA. Urology 1996, 48: 1–3.
 34.
Gleason DF: Classification of prostatic carcinomas. Cancer Chemother Rep 1966, 50: 125–128.
 35.
Stephenson AJ, Kattan MW, Eastham JA, Bianco FJ, Yossepowitch O, Vickers AJ, Klein EA, Wood DP, Scardino PT: Prostate cancer specific mortality after radical prostatectomy for patients treated in the prostatespecific antigen era. Journal of Clinical Oncology 2009, 27: 4300–4305. 10.1200/JCO.2008.18.2501
 36.
Montironi R, Mazzuccheli R, Scarpelli M, LopezBeltran A, Fellegara G, Algaba F: Gleason grading of prostate cancer in needle biopsies or radical prostatectomy specimens: contemporary approach, current clinical significance and sources of pathology discrepancies. BJU International 2005, 95(8):1146–1152. 10.1111/j.1464410X.2005.05540.x
 37.
Allsbrook WC, Mangold KA, Johnson MH, Lane RB, Lane CG, Amin MB, Bostwick DG, Humphrey PA, Jones EC, Reuter VE, Sakr W, Sesterhenn IA, Troncoso P, Wheeler TM, Epstein JI: Interobserver reproducibility of Gleason grading of prostatic carcinoma: Urologic pathologists. Human Pathology 2001, 32: 74–80. 10.1053/hupa.2001.21134
 38.
King CR: Patterns of prostate cancer biopsy grading: Trends and clinical implications. International Journal of Cancer 2000, 90(6):305–311. 10.1002/10970215(20001220)90:6<305::AIDIJC1>3.0.CO;2U
 39.
Doyle S, Hwang M, Shah K, Madabhushi A, Tomaszewski J, Feldman M: Automated Grading of Prostate Cancer using Architectural and Textural Image Features. IEEE International Symposium on Biomedical Imaging (ISBI) 2007, 1284–87.
 40.
Tabesh A, Teverovskiy M, Pang HY, Kumar V, Verbel D, Kotsianti A, Saidi O: Multifeature Prostate Cancer Diagnosis and Gleason Grading of Histological Images. Medical Imaging, IEEE Transactions on 2007, 26(10):1366–1378.
 41.
Sved PD, Gomez P, Manoharan M, Kim SS, Soloway MS: Limitations Of Biopsy Gleason Grade: Implications For Counseling Patients With Biopsy Gleason Score 6 Prostate Cancer. The Journal Of Urology 2004, 172: 98–102. 10.1097/01.ju.0000132135.18093.d6
 42.
Fredolini C, Liotta LA, Petricoin EF: Application of proteomic technologies for prostate cancer detection, prognosis, and tailored therapy. Critical Reviews in Clinical Laboratory Sciences 2010, 47(3):125–138. 10.3109/10408363.2010.503558
 43.
Ornstein DK, Tyson DR: Proteomics for the identification of new prostate cancer biomarkers. Urologic Oncology: Seminars and Original Investigations 2006, 24(3):231–236. 10.1016/j.urolonc.2005.11.035
 44.
Veenstra TD, Conrads TP, Hood BL, Avellino AM, Ellenbogen RG, Morrison RS: Biomarkers: Mining the Biofluid Proteome. Molecular & Cellular Proteomics 2005, 4(4):409–418. 10.1074/mcp.M500006MCP200
 45.
Adam BL, Qu Y, Davis JW, Ward MD, Clements MA, Cazares LH, Semmes OJ, Schellhammer PF, Yasui Y, Feng Z, Wright GL: Serum Protein Fingerprinting Coupled with a Patternmatching Algorithm Distinguishes Prostate Cancer from Benign Prostate Hyperplasia and Healthy Men. Cancer Research 2002, 62(13):3609–3614.
 46.
AlRuwaili JA, Larkin SE, Zeidan BA, Taylor MG, Adra CN, AukimHastie Cl, Townsend PA: Discovery of Serum Protein Biomarkers for Prostate Cancer Progression by Proteomic Analysis. Cancer Genomics  Proteomics 2010, 7(2):93–103.
 47.
Tolonen TT, Tammela TL, Kujala PM, Tuominen VJ, Isola JJ, Visakorpi T: Histopathological variables and biomarkers enhancer of zeste homologue 2, Ki67 and minichromosome maintenance protein 7 as prognosticators in primarily endocrinetreated prostate cancer. BJU International 2011, in press.
 48.
Borga M, Landelius T, Knutsson H: A Unified Approach to PCA, PLS, MLR and CCA. 1997. Tech. rep., Report LiTHISYR1992, ISY, SE581 83 Linkoping, Sweden
 49.
Abdi H: Partial least squares (PLS) regression. Encyclopedia of Social Sciences Research Methods 2003, 1–7.
 50.
Rosipal R, Kramer N: Overview and Recent Advances in Partial Least Squares. Subspace, Latent Structure and Feature Selection 2006, 3940: 34–51. 10.1007/11752790_2
 51.
Hotelling H: Relations between two sets of variants. Biometrika 1936, 28: 321–377.
 52.
Sun L, Ji S, Ye J: A least squares formulation for canonical correlation analysis. ICML 2008, 33: 1024–1031.
 53.
Vinod HD: Canonical ridge and econometrics of joint production. Journal of Econometrics 1976, 4(2):147–166. 10.1016/03044076(76)900105
 54.
Leurgans SE, Moyeed RA, Silverman BW: Canonical Correlation Analysis when the Data are Curves. Journal of the Royal Statistical Society Series B (Methodological) 1993, 55(3):725–740.
 55.
Guo Y, Hastie T, Tibshirani R: Regularized linear discriminant analysis and its application in microarrays. Biostatistics 2007, 8: 86–100.
 56.
Yates RD, Goodman D: Probability and Stochastic Processes: A Friendly Introduction for Electrical and Computer Engineers. John Wiley and Sons; 2005.
 57.
Jafari P, Azuaje F: An assessment of recently published gene expression data analyses: reporting experimental design and statistical factors. BMC Medical Informatics and Decision Making 2006, 6: 27. 10.1186/14726947627
 58.
Thomas JG, Olson JM, Tapscott SJ, Zhao LP: An efficient and robust statistical modeling approach to discover differentially expressed genes using genomic expression profiles. Genome Res 2001, 11: 1227–1236. 10.1101/gr.165101
 59.
Hwang D, Schmitt WA, Stephanopoulos G, Stephanopoulos G: Determination of minimum sample size and discriminatory expression patterns in microarray data. Bioinformatics 2002, 18: 1184–1193. 10.1093/bioinformatics/18.9.1184
 60.
Foster DP, Kakade SM, Zhang T: Multiview dimensionality reduction via canonical correlation analysis. Technical Report TR2008–4, TTIChicago 2008.
 61.
Borga M, Friman O, Lundberg P, Knutsson H: Blind Source Separation of Functional MRI Data. SSBA 2002.
 62.
Heaton K, Master S: Peptide Extraction from FormalinFixed ParaffinEmbedded Tissue. Current Protocols in Protein Science, supplement 65, Unit 23.5 2011, in press.
 63.
Wisniewski JR, Zougman A, Nagaraj N, Mann M: Universal sample preparation method for proteome analysis. Nature Methods 2009, 6(5):359–362. 10.1038/nmeth.1322
 64.
Rappsilber J, Mann M, Ishihama Y: Protocol for micropurification, enrichment, prefractionation and storage of peptides for proteomics using StageTips. Nature Protocols 2007, 2(8):1896–1906. 10.1038/nprot.2007.261
 65.
Doyle S, Feldman M, Tomaszewski J, Shih N, Madabhushi A: Cascaded MultiClass Pairwise Classifier (CascaMPa) For Normal, Cancerous, And Cancer Confounder Classes In Prostate Histology. IEEE International Symposium on Biomedical Imaging (ISBI) 2011, 715–718.
 66.
Sparks R, Madabhushi A: Novel Morphometric based Classification via Diffeomorphic based Shape Representation using Manifold Learning. In International Conference on Medical Image Computing and ComputerAssisted Intervention (MICCAI), Volume 6363. Springer Verlag, Beijing, China: Springer Verlag; 2010:658–665.
 67.
Monaco J, Tomaszewski J, Feldman M, Moradi M, Mousavi P, Boag A, Davidson C, Abolmaesumi P, Madabhushi A: Detection of Prostate Cancer from WholeMount Histology Images Using Markov Random Fields. In Workshop on Microscopic Image Analysis with Applications in Biology (in conjunction with MICCAI). New York, NY; 2008.
 68.
Monaco J, Tomaszewski J, Feldman M, Hagemann I, Moradi M, Mousavi P, Boag A, Davidson C, Abolmaesumi P, Madabhushi A: Highthroughput detection of prostate cancer in histological sections using probabilistic pairwise Markov models. Medical Image Analysis 2010, 14(4):617–629. 10.1016/j.media.2010.04.007
 69.
Basavanhally A, Ganesan S, Agner S, Monaco J, Feldman M, Tomaszewski J, Bhanot G, Madabhushi A: Computerized imagebased detection and grading of lymphocytic infiltration in HER2+ breast cancer histopathology. IEEE Transactions on Biomedical Engineering 2010, 57: 642–653.
 70.
Mukherjee S, Tamayo P, Rogers S, Rifkin R, Engle A, Campbell C, Golub TR, Mesirov JP: Estimating Dataset Size Requirements for Classifying DNA Microarray Data. Journal of Computational Biology 2003, 10(2):119–142. 10.1089/106652703321825928
 71.
Basavanhally A, Doyle S, Madabhushi A: Predicting Classifier Performance With a Small Training Set: Applications to ComputerAided Diagnosis and Prognosis. In IEEE International Symposium on Biomedical Imaging (ISBI). IEEE, Rotterdam, NL: IEEE; 2010:229–232.
Acknowledgements
This work was made possible by grants by the Walter H. Coulter Foundation, National Cancer Institute (Grant Nos. R01CA136535, R01CA140772, and R03CA143991), Department of Defense (W81XWH0810145), The Cancer Institute of New Jersey and the Society for Imaging Informatics in Medicine.
Author information
Affiliations
Corresponding author
Additional information
Authors' contributions
AM and AG devised the methodology and formulated the experiments. AG drafted the manuscript in collaboration with GL. AM edited the manuscript. SRM, MDF, JET, and JWS provided the data and the clinical expertise. All authors have read and approved the final manuscript.
Authors’ original submitted files for images
Below are the links to the authors’ original submitted files for images.
Rights and permissions
Open Access This article is published under license to BioMed Central Ltd. This is an Open Access article is distributed under the terms of the Creative Commons Attribution License ( https://creativecommons.org/licenses/by/2.0 ), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.
About this article
Cite this article
Golugula, A., Lee, G., Master, S.R. et al. Supervised Regularized Canonical Correlation Analysis: integrating histologic and proteomic measurements for predicting biochemical recurrence following prostate surgery. BMC Bioinformatics 12, 483 (2011). https://doi.org/10.1186/1471210512483
Received:
Accepted:
Published:
Keywords
 Principal Component Analysis
 Radical Prostatectomy
 Partial Little Square Regression
 Canonical Correlation Analysis
 Biochemical Recurrence