Análise de componentes principais

PCA de uma distribuição Gaussiana multivariada centrada em (1,3) com um desvio padrão de 3 aproximadamente na direção (0.878, 0.478) e desvio padrão 1 na direção ortogonal. Os vetores na figura são os autovetores da matriz de covariância multiplicados pela raiz quadrada do autovalor correspondente, e transladados de forma a iniciarem na média.

A Análise de Componententes Principais ou principal component analysis (PCA) é um procedimento matemático que utiliza uma transformação ortogonal para converter um conjunto de observações de variáveis possívelmente correlacionadas a um conjunto de valores de variáveis linearmente descorrelacionadas chamadas componentes principais. O número de componentes principais é menor ou igual ao número de variáveis originais. Esta transformação é definida de forma que o primeiro componente principal tem a maior variância possível (ou seja, é responsável pelo máximo de variabilidade nos dados), e cada componente seguinte, por sua vez, tem a máxima variância sob a restrição de ser ortogonal a (i.e., não-correlacionado com) os componentes anteriores. Os componentes principais são garantidamente independentes apenas se os dados forem normalmente distribuídos (conjuntamente). O PCA é sensível à escala relativa das variáveis originais. Dependendo da área de aplicação, o PCA é também conhecido pela transformada Karhunen–Loève (KLT) discreta,transformada de Hotelling ou decomposição ortogonal própria (POD).

O PCA foi inventado em 1901 por Karl Pearson. Agora, é mais comumente usado como uma ferramenta de análise exploratória de dados e para fazer modelos preditivos. PCA pode ser feito por decomposição em autovalores de uma matriz de covariância (ou de correlação) ou por decomposição em valores singulares de uma matrix de dados, geralmente depois de centralizar (e normalizar ou usar pontuações-Z) a matriz de dados para cada atributo.. Os resultados de PCA são geralmente discutidos em termos pontuações de componentes, também chamados de pontuações de fatores (os valores de variável transfomados correspondem a um ponto de dado particular), e carregamentos (loadings), i.e., o peso pelo qual cada variável normalizada original deve ser multiplicada para se obter a pontuação de componente).

O PCA é a mais simples das verdadeiras análises multivariadas por autovetores. Com frequência, sua operação pode ser tomada como sendo reveladora da estrutura interna dos dados, de uma forma que melhor explica a variânica nos dados. Se visualizarmos um conjunto de dados multivariados em um espaço de alta dimensão, com 1 eixo por variável, o PCA pode ser usado para fornecer uma visualização em dimensões mais baixas dos mesmos dados, uma verdadeira "sombra" do objeto original quando visto de seu ponto mais informativo. Isto é feito usando-se apenas os primeiros componentes principais, de forma que a dimensionalidade dos dados tranformados é reduzida.

O PCA é fortemente ligado à análise de fatores; de fato, alguns pacotes estatísticos propositadamente confluem as técnicas. A verdadeira análise de fatores faz assunções diferentes sobre a estrutura subjacente dos dados e encontra os autovetores de uma matriz levemente diferente.

Análise_de_Componentes_Principais

Detalhes

O PCA é matematicamente definido como uma transformação linear ortogonal que transforma os dados para um novo sistema de coordenadas de forma que a maior variância por qualquer projeção dos dados fica ao longo da primeira coordenada (o chamado primeiro componente), a segunda maior variância fica ao longo da segunda coordenada, e assim por diante.

Define a data matrix, X^T, with zero empirical mean (the empirical (sample) mean of the distribution has been subtracted from the data set), where each of the n rows represents a different repetition of the experiment, and each of the m columns gives a particular kind of datum (say, the results from a particular probe). (Note that X^T is defined here and not X itself, and what we are calling X^T is often alternatively denoted as X itself.) The singular value decomposition of X is X = WΣV^T, where the m × m matrix W is the matrix of eigenvectors of the covariance matrix XX^T, the matrix Σ is an m × n rectangular diagonal matrix with nonnegative real numbers on the diagonal, and the n × n matrix V is the matrix of eigenvectors of X^TX. The PCA transformation that preserves dimensionality (that is, gives the same number of principal components as original variables) is then given by:

${\begin{aligned}\mathbf {Y} ^{\top }&=\mathbf {X} ^{\top }\mathbf {W} \\&=\mathbf {V} \mathbf {\Sigma } ^{\top }\mathbf {W} ^{\top }\mathbf {W} \\&=\mathbf {V} \mathbf {\Sigma } ^{\top }\end{aligned}}$

V is not uniquely defined in the usual case when m < n − 1, but Y will usually still be uniquely defined. Since W (by definition of the SVD of a real matrix) is an orthogonal matrix, each row of Y^T is simply a rotation of the corresponding row of X^T. The first column of Y^T is made up of the "scores" of the cases with respect to the "principal" component, the next column has the scores with respect to the "second principal" component, and so on.

If we want a reduced-dimensionality representation, we can project X down into the reduced space defined by only the first L singular vectors, W_L:

$\mathbf {Y} =\mathbf {W_{L}} ^{\top }\mathbf {X} =\mathbf {\Sigma _{L}} \mathbf {V} ^{\top }$ where $\mathbf {\Sigma _{L}} =\mathbf {I} _{L\times m}\mathbf {\Sigma }$ with $\mathbf {I} _{L\times m}$ the $L\times m$ rectangular identity matrix.

The matrix W of singular vectors of X is equivalently the matrix W of eigenvectors of the matrix of observed covariances C = X X^T,

$\mathbf {X} \mathbf {X} ^{\top }=\mathbf {W} \mathbf {\Sigma } \mathbf {\Sigma } ^{\top }\mathbf {W} ^{\top }$

Given a set of points in Euclidean space, the first principal component corresponds to a line that passes through the multidimensional mean and minimizes the sum of squares of the distances of the points from the line. The second principal component corresponds to the same concept after all correlation with the first principal component has been subtracted from the points. The singular values (in Σ) are the square roots of the eigenvalues of the matrix XX^T. Each eigenvalue is proportional to the portion of the "variance" (more correctly of the sum of the squared distances of the points from their multidimensional mean) that is correlated with each eigenvector. The sum of all the eigenvalues is equal to the sum of the squared distances of the points from their multidimensional mean. PCA essentially rotates the set of points around their mean in order to align with the principal components. This moves as much of the variance as possible (using an orthogonal transformation) into the first few dimensions. The values in the remaining dimensions, therefore, tend to be small and may be dropped with minimal loss of information. PCA is often used in this manner for dimensionality reduction. PCA has the distinction of being the optimal orthogonal transformation for keeping the subspace that has largest "variance" (as defined above). This advantage, however, comes at the price of greater computational requirements if compared, for example and when applicable, to the discrete cosine transform. Nonlinear dimensionality reduction techniques tend to be more computationally demanding than PCA.

PCA is sensitive to the scaling of the variables. If we have just two variables and they have the same sample variance and are positively correlated, then the PCA will entail a rotation by 45° and the "loadings" for the two variables with respect to the principal component will be equal. But if we multiply all values of the first variable by 100, then the principal component will be almost the same as that variable, with a small contribution from the other variable, whereas the second component will be almost aligned with the second original variable. This means that whenever the different variables have different units (like temperature and mass), PCA is a somewhat arbitrary method of analysis. (Different results would be obtained if one used Fahrenheit rather than Celsius for example.) Note that Pearson's original paper was entitled "On Lines and Planes of Closest Fit to Systems of Points in Space" – "in space" implies physical Euclidean space where such concerns do not arise. One way of making the PCA less arbitrary is to use variables scaled so as to have unit variance.

Discussion

Mean subtraction (a.k.a. "mean centering") is necessary for performing PCA to ensure that the first principal component describes the direction of maximum variance. If mean subtraction is not performed, the first principal component might instead correspond more or less to the mean of the data. A mean of zero is needed for finding a basis that minimizes the mean square error of the approximation of the data.

Assuming zero empirical mean (the empirical mean of the distribution has been subtracted from the data set), the principal component w₁ of a data set X can be defined as:

$\mathbf {w} _{1}={\underset {\Vert \mathbf {w} \Vert =1}{\operatorname {\arg \,max} }}\,\operatorname {Var} \{\mathbf {w} ^{\top }\mathbf {X} \}={\underset {\Vert \mathbf {w} \Vert =1}{\operatorname {\arg \,max} }}\,E\left\{\left(\mathbf {w} ^{\top }\mathbf {X} \right)^{2}\right\}$

(See arg max for the notation.) With the first k − 1 components, the kth component can be found by subtracting the first $k-1$ principal components from X:

$\mathbf {\hat {X}} _{k-1}=\mathbf {X} -\sum _{i=1}^{k-1}\mathbf {w} _{i}\mathbf {w} _{i}^{\top }\mathbf {X}$

and by substituting this as the new data set to find a principal component in

$\mathbf {w} _{k}={\underset {\Vert \mathbf {w} \Vert =1}{\operatorname {arg\,max} }}\,E\left\{\left(\mathbf {w} ^{\top }\mathbf {\hat {X}} _{k-1}\right)^{2}\right\}.$

PCA is equivalent to empirical orthogonal functions (EOF), a name which is used in meteorology.

An autoencoder neural network with a linear hidden layer is similar to PCA. Upon convergence, the weight vectors of the K neurons in the hidden layer will form a basis for the space spanned by the first K principal components. Unlike PCA, this technique will not necessarily produce orthogonal vectors.

PCA is a popular primary technique in pattern recognition. It is not, however, optimized for class separability. An alternative is the linear discriminant analysis, which does take this into account.

Table of symbols and abbreviations

Symbol	Meaning	Dimensions	Indices
$\mathbf {X} =\{X[m,n]\}$	data matrix, consisting of the set of all data vectors, one vector per column	$M\times N$	$m=1\ldots M$ $n=1\ldots N$
$N\,$	the number of column vectors in the data set	$1\times 1$	scalar
$M\,$	the number of elements in each column vector (dimension)	$1\times 1$	scalar
$L\,$	the number of dimensions in the dimensionally reduced subspace, $1\leq L\leq M$	$1\times 1$	scalar
$\mathbf {u} =\{u[m]\}$	vector of empirical means, one mean for each row m of the data matrix	$M\times 1$	$m=1\ldots M$
$\mathbf {s} =\{s[m]\}$	vector of empirical standard deviations, one standard deviation for each row m of the data matrix	$M\times 1$	$m=1\ldots M$
$\mathbf {h} =\{h[n]\}$	vector of all 1's	$1\times N$	$n=1\ldots N$
$\mathbf {B} =\{B[m,n]\}$	deviations from the mean of each row m of the data matrix	$M\times N$	$m=1\ldots M$ $n=1\ldots N$
$\mathbf {Z} =\{Z[m,n]\}$	z-scores, computed using the mean and standard deviation for each row m of the data matrix	$M\times N$	$m=1\ldots M$ $n=1\ldots N$
$\mathbf {C} =\{C[p,q]\}$	covariance matrix	$M\times M$	$p=1\ldots M$ $q=1\ldots M$
$\mathbf {R} =\{R[p,q]\}$	correlation matrix	$M\times M$	$p=1\ldots M$ $q=1\ldots M$
$\mathbf {V} =\{V[p,q]\}$	matrix consisting of the set of all eigenvectors of C, one eigenvector per column	$M\times M$	$p=1\ldots M$ $q=1\ldots M$
$\mathbf {D} =\{D[p,q]\}$	diagonal matrix consisting of the set of all eigenvalues of C along its principal diagonal, and 0 for all other elements	$M\times M$	$p=1\ldots M$ $q=1\ldots M$
$\mathbf {W} =\{W[p,q]\}$	matrix of basis vectors, one vector per column, where each basis vector is one of the eigenvectors of C, and where the vectors in W are a sub-set of those in V	$M\times L$	$p=1\ldots M$ $q=1\ldots L$
$\mathbf {Y} =\{Y[m,n]\}$	matrix consisting of N column vectors, where each vector is the projection of the corresponding data vector from matrix X onto the basis vectors contained in the columns of matrix W.	$L\times N$	$m=1\ldots L$ $n=1\ldots N$

Properties and limitations of PCA

As noted above, the results of PCA depend on the scaling of the variables.

The applicability of PCA is limited by certain assumptions made in its derivation.

Computing PCA using the covariance method

The following is a detailed description of PCA using the covariance method (see also here). But note that it is better to use the singular value decomposition (using standard software).

The goal is to transform a given data set X of dimension M to an alternative data set Y of smaller dimension L. Equivalently, we are seeking to find the matrix Y, where Y is the Karhunen–Loève transform (KLT) of matrix X:

$\mathbf {Y} =\mathbb {KLT} \{\mathbf {X} \}$

Organize the data set

Suppose you have data comprising a set of observations of M variables, and you want to reduce the data so that each observation can be described with only L variables, L < M. Suppose further, that the data are arranged as a set of N data vectors $\mathbf {x} _{1}\ldots \mathbf {x} _{N}$ with each $\mathbf {x} _{n}$ representing a single grouped observation of the M variables.

• Write $\mathbf {x} _{1}\ldots \mathbf {x} _{N}$ as column vectors, each of which has M rows.
• Place the column vectors into a single matrix X of dimensions M × N.

Calculate the empirical mean

• Find the empirical mean along each dimension m = 1, ..., M.
• Place the calculated mean values into an empirical mean vector u of dimensions M × 1.

$u[m]={1 \over N}\sum _{n=1}^{N}X[m,n]$

Calculate the deviations from the mean

Mean subtraction is an integral part of the solution towards finding a principal component basis that minimizes the mean square error of approximating the data. Hence we proceed by centering the data as follows:

• Subtract the empirical mean vector u from each column of the data matrix X.
• Store mean-subtracted data in the M × N matrix B.

$\mathbf {B} =\mathbf {X} -\mathbf {u} \mathbf {h}$

where h is a 1 × N row vector of all 1s:

$h[n]=1\,\qquad \qquad {\text{for }}n=1,\ldots ,N$

Find the covariance matrix

• Find the M × M empirical covariance matrix C from the outer product of matrix B with itself:

$\mathbf {C} =\mathbb {E} \left[\mathbf {B} \otimes \mathbf {B} \right]=\mathbb {E} \left[\mathbf {B} \cdot \mathbf {B} ^{*}\right]={1 \over N}\sum _{}\mathbf {B} \cdot \mathbf {B} ^{*}$

where

$\mathbb {E}$ is the expected value operator,

$\otimes$ is the outer product operator, and

$*\$ is the conjugate transpose operator. Note that if B consists entirely of real numbers, which is the case in many applications, the "conjugate transpose" is the same as the regular transpose.

• Please note that the information in this section is indeed a bit fuzzy. Outer products apply to vectors. For tensor cases we should apply tensor products, but the covariance matrix in PCA is a sum of outer products between its sample vectors; indeed, it could be represented as B.B*. See the covariance matrix sections on the discussion page for more information.

Find the eigenvectors and eigenvalues of the covariance matrix

• Compute the matrix V of eigenvectors which diagonalizes the covariance matrix C:

$\mathbf {V} ^{-1}\mathbf {C} \mathbf {V} =\mathbf {D}$

where D is the diagonal matrix of eigenvalues of C. This step will typically involve the use of a computer-based algorithm for computing eigenvectors and eigenvalues. These algorithms are readily available as sub-components of most matrix algebra systems, such as R (programming language), MATLAB, Mathematica, SciPy, IDL(Interactive Data Language), or GNU Octave as well as OpenCV.

• Matrix D will take the form of an M × M diagonal matrix, where

$D[p,q]=\lambda _{m}\qquad {\text{for }}p=q=m$

is the mth eigenvalue of the covariance matrix C, and

$D[p,q]=0\qquad {\text{for }}p\neq q.$

• Matrix V, also of dimension M × M, contains M column vectors, each of length M, which represent the M eigenvectors of the covariance matrix C.
• The eigenvalues and eigenvectors are ordered and paired. The mth eigenvalue corresponds to the mth eigenvector.

Rearrange the eigenvectors and eigenvalues

• Sort the columns of the eigenvector matrix V and eigenvalue matrix D in order of decreasing eigenvalue.
• Make sure to maintain the correct pairings between the columns in each matrix.

Compute the cumulative energy content for each eigenvector

• The eigenvalues represent the distribution of the source data's energy among each of the eigenvectors, where the eigenvectors form a basis for the data. The cumulative energy content g for the mth eigenvector is the sum of the energy content across all of the eigenvalues from 1 through m:

$g[m]=\sum _{q=1}^{m}D[q,q]\qquad \mathrm {for} \qquad m=1,\dots ,M$^{[carece de fontes]}

Select a subset of the eigenvectors as basis vectors

• Save the first L columns of V as the M × L matrix W:

$W[p,q]=V[p,q]\qquad \mathrm {for} \qquad p=1,\dots ,M\qquad q=1,\dots ,L$

where

$1\leq L\leq M.$

• Use the vector g as a guide in choosing an appropriate value for L. The goal is to choose a value of L as small as possible while achieving a reasonably high value of g on a percentage basis. For example, you may want to choose L so that the cumulative energy g is above a certain threshold, like 90 percent. In this case, choose the smallest value of L such that

${\frac {g[m=L]}{\sum _{q=1}^{M}D[q,q]}}\geq 0.9\,$

Convert the source data to z-scores

• Create an M × 1 empirical standard deviation vector s from the square root of each element along the main diagonal of the covariance matrix C:

$\mathbf {s} =\{s[m]\}=\{{\sqrt {C[m,m]}}\}\qquad {\text{for }}m=1,\ldots ,M$

• Calculate the M × N z-score matrix:

$\mathbf {Z} ={\mathbf {B} \over \mathbf {s} \cdot \mathbf {h} }$ (divide element-by-element)

• Note: While this step is useful for various applications as it normalizes the data set with respect to its variance, it is not integral part of PCA/KLT

Project the z-scores of the data onto the new basis

• The projected vectors are the columns of the matrix

$\mathbf {Y} =\mathbf {W} ^{*}\cdot \mathbf {Z} =\mathbb {KLT} \{\mathbf {X} \}.$

• W* is the conjugate transpose of the eigenvector matrix.
• The columns of matrix Y represent the Karhunen–Loeve transforms (KLT) of the data vectors in the columns of matrix X.

Derivation of PCA using the covariance method

Let X be a d-dimensional random vector expressed as column vector. Without loss of generality, assume X has zero mean.

We want to find $(\ast )\,$ a $d\times d$ orthonormal transformation matrix P so that PX has a diagonal covariant matrix (i.e. PX is a random vector with all its distinct components pairwise uncorrelated).

A quick computation assuming $P$ were unitary yields:

${\begin{array}{rcl}\operatorname {cov} (PX)&=&\mathbb {E} [PX~(PX)^{\dagger }]\\&=&\mathbb {E} [PX~X^{\dagger }P^{\dagger }]\\&=&P~\mathbb {E} [XX^{\dagger }]P^{\dagger }\\&=&P~\operatorname {cov} (X)P^{-1}\\\end{array}}$

Hence $(\ast )\,$ holds if and only if $\operatorname {cov} (X)$ were diagonalisable by $P$.

This is very constructive, as cov(X) is guaranteed to be a non-negative definite matrix and thus is guaranteed to be diagonalisable by some unitary matrix.

Computing principal components efficiently

Iterative computation

In practical implementations especially with high dimensional data (large m), the covariance method is rarely used because it is not efficient. One way to compute the first principal component efficiently is shown in the following pseudo-code, for a data matrix X^T with zero mean, without ever computing its covariance matrix. Note that here a zero mean data matrix means that the columns of X^T should each have zero mean.

$\mathbf {p} =$ a random vector
do c times:
      $\mathbf {t} =0$ (a vector of length m)
      for each row $\mathbf {x} \in \mathbf {X^{T}}$
            $\mathbf {t} =\mathbf {t} +(\mathbf {x} \cdot \mathbf {p} )\mathbf {x}$
      $\mathbf {p} ={\frac {\mathbf {t} }{|\mathbf {t} |}}$
return $\mathbf {p}$

This algorithm is simply an efficient way of calculating XX^Tp, normalizing, and placing the result back in p (Power iteration). It avoids the nm² operations of calculating the covariance matrix. p will typically get close to the first principal component of X^T within a small number of iterations, c. (The magnitude of t will be larger after each iteration. Convergence can be detected when it increases by an amount too small for the precision of the machine.)

Subsequent principal components can be computed by subtracting component p from X^T (see Gram–Schmidt) and then repeating this algorithm to find the next principal component. However this simple approach is not numerically stable if more than a small number of principal components are required, because imprecisions in the calculations will additively affect the estimates of subsequent principal components. More advanced methods build on this basic idea, as with the closely related Lanczos algorithm.

One way to compute the eigenvalue that corresponds with each principal component is to measure the difference in sum-squared-distance between the rows and the mean, before and after subtracting out the principal component. The eigenvalue that corresponds with the component that was removed is equal to this difference.

The NIPALS method

Ver artigo principal: Non-linear iterative partial least squares

For very high-dimensional datasets, such as those generated in the *omics sciences (e.g., genomics, metabolomics) it is usually only necessary to compute the first few PCs. The non-linear iterative partial least squares (NIPALS) algorithm calculates t₁ and p₁' from X. The outer product, t₁p₁' can then be subtracted from X leaving the residual matrix E₁. This can be then used to calculate subsequent PCs. This results in a dramatic reduction in computational time since calculation of the covariance matrix is avoided.

Online/sequential estimation

In an "online" or "streaming" situation with data arriving piece by piece rather than being stored in a single batch, it is useful to make an estimate of the PCA projection that can be updated sequentially. This can be done efficiently, but requires different algorithms.

Relation between PCA and K-means clustering

It has been shown recently (2001,2004) that the relaxed solution of K-means clustering, specified by the cluster indicators, is given by the PCA principal components, and the PCA subspace spanned by the principal directions is identical to the cluster centroid subspace specified by the between-class scatter matrix. Thus PCA automatically projects to the subspace where the global solution of K-means clustering lies, and thus facilitates K-means clustering to find near-optimal solutions.

Correspondence analysis

Correspondence analysis (CA) was developed by Jean-Paul Benzécri and is conceptually similar to PCA, but scales the data (which should be non-negative) so that rows and columns are treated equivalently. It is traditionally applied to contingency tables. CA decomposes the chi-squared statistic associated to this table into orthogonal factors. Because CA is a descriptive technique, it can be applied to tables for which the chi-squared statistic is appropriate or not. Several variants of CA are available including detrended correspondence analysis and canonical correspondence analysis. One special extension is multiple correspondence analysis, which may be seen as the counterpart of principal component analysis for categorical data.

Generalizations

Nonlinear generalizations

Linear PCA versus nonlinear Principal Manifolds for visualization of breast cancer microarray data: a) Configuration of nodes and 2D Principal Surface in the 3D PCA linear manifold. The dataset is curved and cannot be mapped adequately on a 2D principal plane; b) The distribution in the internal 2D non-linear principal surface coordinates (ELMap2D) together with an estimation of the density of points; c) The same as b), but for the linear 2D PCA manifold (PCA2D). The "basal" breast cancer subtype is visualized more adequately with ELMap2D and some features of the distribution become better resolved in comparison to PCA2D. Principal manifolds are produced by the elastic maps algorithm. Data are available for public competition.

Most of the modern methods for nonlinear dimensionality reduction find their theoretical and algorithmic roots in PCA or K-means. Pearson's original idea was to take a straight line (or plane) which will be "the best fit" to a set of data points. Principal curves and manifolds give the natural geometric framework for PCA generalization and extend the geometric interpretation of PCA by explicitly constructing an embedded manifold for data approximation, and by encoding using standard geometric projection onto the manifold, as it is illustrated by Fig. See also the elastic map algorithm and principal geodesic analysis.

Multilinear generalizations

In multilinear subspace learning, PCA is generalized to multilinear PCA (MPCA) that extracts features directly from tensor representations. MPCA is solved by performing PCA in each mode of the tensor iteratively. MPCA has been applied to face recognition, gait recognition, etc. MPCA is further extended to uncorrelated MPCA, non-negative MPCA and robust MPCA.

Higher order

N-way principal component analysis may be performed with models such as Tucker decomposition, PARAFAC, multiple factor analysis, co-inertia analysis, STATIS, and DISTATIS.

Robustness - Weighted PCA

While PCA finds the mathematically optimal method (as in minimizing the squared error), it is sensitive to outliers in the data that produce large errors PCA tries to avoid. It therefore is common practice to remove outliers before computing PCA. However, in some contexts, outliers can be difficult to identify. For example in data mining algorithms like correlation clustering, the assignment of points to clusters and outliers is not known beforehand. A recently proposed generalization of PCA based on a Weighted PCA increases robustness by assigning different weights to data objects based on their estimated relevancy.

Software/source code

• Cornell Spectrum Imager - An open-source toolset built on ImageJ. Enables quick easy PCA analysis for 3D datacubes.
• imDEV Free Excel addin to calculate principal components using R package pcaMethods.
• "ViSta: The Visual Statistics System" a free software that provides principal components analysis, simple and multiple correspondence analysis.
• "Spectramap" is software to create a biplot using principal components analysis, correspondence analysis or spectral map analysis.
• XLSTAT is a statistical and multivariate analysis software including Principal Component Analysis among other multivariate tools.
• FinMath, a .NET numerical library containing an implementation of PCA.
• The Unscrambler is a multivariate analysis software enabling Principal Component Analysis (PCA) with PCA Projection.
• Computer Vision Library
• In the MATLAB Statistics Toolbox, the functions princomp and wmspca give the principal components, while the function pcares gives the residuals and reconstructed matrix for a low-rank PCA approximation. Here is a link to a MATLAB implementation of PCA PcaPress .
• In the NAG Library, principal components analysis is implemented via the g03aa routine (available in both the Fortran and the C versions of the Library).
• NMath, a numerical library containing PCA for the .NET Framework.
• in Octave, a free software computational environment mostly compatible with MATLAB, the function princomp gives the principal component.
• in the free statistical package R, the functions princomp and prcomp can be used for principal component analysis; prcomp uses singular value decomposition which generally gives better numerical accuracy. Recently there has been an explosion in implementations of principal component analysis in various R packages, generally in packages for specific purposes. For a more complete list, see here: [1].
• In XLMiner, the Principal Components tab can be used for principal component analysis.
• In IDL, the principal components can be calculated using the function pcomp.
• Weka computes principal components (javadoc).
• Software for analyzing multivariate data with instant response using PCA
• Orange (software) supports PCA through its Linear Projection widget.
• A version of PCA adapted for population genetics analysis can be found in the suite EIGENSOFT.
• PCA can also be performed by the statistical software Partek Genomics Suite, developed by Partek.

See also

• Multilinear PCA
• Correspondence analysis
• Eigenface
• Exploratory factor analysis (Wikiversity)
• Geometric data analysis
• Factorial code
• Independent component analysis
• Kernel PCA
• Matrix decomposition
• Nonlinear dimensionality reduction
• Oja's rule
• Point distribution model (PCA applied to morphometry and computer vision)
• Principal component regression
• Principal component analysis (Wikibooks)
• Singular spectrum analysis
• Singular value decomposition
• Sparse PCA
• Transform coding
• Weighted least squares
• Dynamic mode decomposition
• Low-rank approximation

References

• Jolliffe, I. T. (1986). Principal Component Analysis. [S.l.]: Springer-Verlag. 487 páginas. ISBN 978-0-387-95442-4. doi:10.1007/b98835