The method of least squares is a parameter estimation method in regression analysis based on minimizing the sum of the squares of the residuals (a residual being the difference between an observed value and the fitted value provided by a model) made in the results of each individual equation.
The most important application is in data fitting. When the problem has substantial uncertainties in the independent variable (the x variable), then simple regression and leastsquares methods have problems; in such cases, the methodology required for fitting errorsinvariables models may be considered instead of that for least squares.
Least squares problems fall into two categories: linear or ordinary least squares and nonlinear least squares, depending on whether or not the residuals are linear in all unknowns. The linear leastsquares problem occurs in statistical regression analysis; it has a closedform solution. The nonlinear problem is usually solved by iterative refinement; at each iteration the system is approximated by a linear one, and thus the core calculation is similar in both cases.
Polynomial least squares describes the variance in a prediction of the dependent variable as a function of the independent variable and the deviations from the fitted curve.
When the observations come from an exponential family with identity as its natural sufficient statistics and mildconditions are satisfied (e.g. for normal, exponential, Poisson and binomial distributions), standardized leastsquares estimates and maximumlikelihood estimates are identical.^{[1]} The method of least squares can also be derived as a method of moments estimator.
The following discussion is mostly presented in terms of linear functions but the use of least squares is valid and practical for more general families of functions. Also, by iteratively applying local quadratic approximation to the likelihood (through the Fisher information), the leastsquares method may be used to fit a generalized linear model.
The leastsquares method was officially discovered and published by AdrienMarie Legendre (1805),^{[2]} though it is usually also cocredited to Carl Friedrich Gauss (1809),^{[3]} ^{[4]} who contributed significant theoretical advances to the method, and may have also used it in his earlier work in 1794 and 1795.^{[5]}
History
Founding
The method of least squares grew out of the fields of astronomy and geodesy, as scientists and mathematicians sought to provide solutions to the challenges of navigating the Earth's oceans during the Age of Discovery. The accurate description of the behavior of celestial bodies was the key to enabling ships to sail in open seas, where sailors could no longer rely on land sightings for navigation.
The method was the culmination of several advances that took place during the course of the eighteenth century:^{[6]}
 The combination of different observations as being the best estimate of the true value; errors decrease with aggregation rather than increase, perhaps first expressed by Roger Cotes in 1722.
 The combination of different observations taken under the same conditions contrary to simply trying one's best to observe and record a single observation accurately. The approach was known as the method of averages. This approach was notably used by Tobias Mayer while studying the librations of the Moon in 1750, and by PierreSimon Laplace in his work in explaining the differences in motion of Jupiter and Saturn in 1788.
 The combination of different observations taken under conditions. The method came to be known as the method of least absolute deviation. It was notably performed by Roger Joseph Boscovich in his work on the shape of the Earth in 1757 and by PierreSimon Laplace for the same problem in 1789 and 1799.
 The development of a criterion that can be evaluated to determine when the solution with the minimum error has been achieved. Laplace tried to specify a mathematical form of the probability density for the errors and define a method of estimation that minimizes the error of estimation. For this purpose, Laplace used a symmetric twosided exponential distribution we now call Laplace distribution to model the error distribution, and used the sum of absolute deviation as error of estimation. He felt these to be the simplest assumptions he could make, and he had hoped to obtain the arithmetic mean as the best estimate. Instead, his estimator was the posterior median.
The method
The first clear and concise exposition of the method of least squares was published by Legendre in 1805. The technique is described as an algebraic procedure for fitting linear equations to data and Legendre demonstrates the new method by analyzing the same data as Laplace for the shape of the Earth. Within ten years after Legendre's publication, the method of least squares had been adopted as a standard tool in astronomy and geodesy in France, Italy, and Prussia, which constitutes an extraordinarily rapid acceptance of a scientific technique.
In 1809 Carl Friedrich Gauss published his method of calculating the orbits of celestial bodies. In that work he claimed to have been in possession of the method of least squares since 1795.^{[7]} This naturally led to a priority dispute with Legendre. However, to Gauss's credit, he went beyond Legendre and succeeded in connecting the method of least squares with the principles of probability and to the normal distribution. He had managed to complete Laplace's program of specifying a mathematical form of the probability density for the observations, depending on a finite number of unknown parameters, and define a method of estimation that minimizes the error of estimation. Gauss showed that the arithmetic mean is indeed the best estimate of the location parameter by changing both the probability density and the method of estimation. He then turned the problem around by asking what form the density should have and what method of estimation should be used to get the arithmetic mean as estimate of the location parameter. In this attempt, he invented the normal distribution.
An early demonstration of the strength of Gauss's method came when it was used to predict the future location of the newly discovered asteroid Ceres. On 1 January 1801, the Italian astronomer Giuseppe Piazzi discovered Ceres and was able to track its path for 40 days before it was lost in the glare of the Sun. Based on these data, astronomers desired to determine the location of Ceres after it emerged from behind the Sun without solving Kepler's complicated nonlinear equations of planetary motion. The only predictions that successfully allowed Hungarian astronomer Franz Xaver von Zach to relocate Ceres were those performed by the 24yearold Gauss using leastsquares analysis.
In 1810, after reading Gauss's work, Laplace, after proving the central limit theorem, used it to give a large sample justification for the method of least squares and the normal distribution. In 1822, Gauss was able to state that the leastsquares approach to regression analysis is optimal in the sense that in a linear model where the errors have a mean of zero, are uncorrelated, and have equal variances, the best linear unbiased estimator of the coefficients is the leastsquares estimator. This result is known as the Gauss–Markov theorem.
The idea of leastsquares analysis was also independently formulated by the American Robert Adrain in 1808. In the next two centuries workers in the theory of errors and in statistics found many different ways of implementing least squares.^{[8]}
Problem statement
The objective consists of adjusting the parameters of a model function to best fit a data set. A simple data set consists of n points (data pairs)
(x_{i,y}_{i)}
, i = 1, …, n, where
x_{i}
is an independent variable and
y_{i}
is a dependent variable whose value is found by observation. The model function has the form
f(x,\boldsymbol\beta)
, where m adjustable parameters are held in the vector
\boldsymbol\beta
. The goal is to find the parameter values for the model that "best" fits the data. The fit of a model to a data point is measured by its residual, defined as the difference between the observed value of the dependent variable and the value predicted by the model:
r_{i}=y_{i}f(x_{i,}\boldsymbol\beta).
The leastsquares method finds the optimal parameter values by minimizing the sum of squared residuals,
S
:
n  
S=\sum  
i=1 
2.  
r  
i 
In the simplest case
f(x_{i,}\boldsymbol\beta)=\beta
and the result of the leastsquares method is the arithmetic mean of the input data.
An example of a model in two dimensions is that of the straight line. Denoting the yintercept as
\beta_{0}
and the slope as
\beta_{1}
, the model function is given by
f(x,\boldsymbol\beta)=\beta_{0+\beta}_{1}x
. See linear least squares for a fully worked out example of this model.
A data point may consist of more than one independent variable. For example, when fitting a plane to a set of height measurements, the plane is a function of two independent variables, x and z, say. In the most general case there may be one or more independent variables and one or more dependent variables at each data point.
To the right is a residual plot illustrating random fluctuations about
r_{i=0}
, indicating that a linear model
(Y_{i}=\alpha+\betax_{i}+U_{i)}
is appropriate.
U_{i}
is an independent, random variable.^{[9]}
If the residual points had some sort of a shape and were not randomly fluctuating, a linear model would not be appropriate. For example, if the residual plot had a parabolic shape as seen to the right, a parabolic model
(Y_{i}=\alpha+\betax_{i}+\gamma
2  
x  
i 
+U_{i)}
would be appropriate for the data. The residuals for a parabolic model can be calculated via
r_{i=y}_{i\hat{\alpha}\hat{\beta}}x_{i\widehat{\gamma}}
2  
x  
i 
.
Limitations
This regression formulation considers only observational errors in the dependent variable (but the alternative total least squares regression can account for errors in both variables). There are two rather different contexts with different implications:
 Regression for prediction. Here a model is fitted to provide a prediction rule for application in a similar situation to which the data used for fitting apply. Here the dependent variables corresponding to such future application would be subject to the same types of observation error as those in the data used for fitting. It is therefore logically consistent to use the leastsquares prediction rule for such data.
 Regression for fitting a "true relationship". In standard regression analysis that leads to fitting by least squares there is an implicit assumption that errors in the independent variable are zero or strictly controlled so as to be negligible. When errors in the independent variable are nonnegligible, models of measurement error can be used; such methods can lead to parameter estimates, hypothesis testing and confidence intervals that take into account the presence of observation errors in the independent variables.^{[10]} An alternative approach is to fit a model by total least squares; this can be viewed as taking a pragmatic approach to balancing the effects of the different sources of error in formulating an objective function for use in modelfitting.
Solving the least squares problem
The minimum of the sum of squares is found by setting the gradient to zero. Since the model contains m parameters, there are m gradient equations:$$\backslash frac=2\backslash sum\_i\; r\_i\backslash frac\; =\; 0,\backslash \; j=1,\backslash ldots,m,$$and since
r_{i=y}_{if(x}_{i,\boldsymbol}\beta)
, the gradient equations become$$2\backslash sum\_i\; r\_i\backslash frac=0,\backslash \; j=1,\backslash ldots,m.$$
The gradient equations apply to all least squares problems. Each particular problem requires particular expressions for the model and its partial derivatives.^{[11]}
Linear least squares
See main article: Linear least squares.
A regression model is a linear one when the model comprises a linear combination of the parameters, i.e.,$$f(x,\; \backslash boldsymbol\; \backslash beta)\; =\; \backslash sum\_^m\; \backslash beta\_j\; \backslash phi\_j(x),$$where the function
\phi_{j}
is a function of
x
.
Letting
X_{ij}=\phi_{j(x}_{i})
and putting the independent and dependent variables in matrices
X
and
Y
, respectively, we can compute the least squares in the following way. Note that
D
is the set of all data.^{[12]}
$$L(D,\; \backslash boldsymbol)=\; \backslash left\backslash Y\; \; X\backslash boldsymbol\; \backslash right\backslash ^2=\; (Y\; \; X\backslash boldsymbol)^\backslash mathsf\; (Y\; \; X\backslash boldsymbol)=\; Y^\backslash mathsfY\; Y^\backslash mathsfX\backslash boldsymbol\; \backslash boldsymbol^\backslash mathsfX^\backslash mathsfY+\backslash boldsymbol^\backslash mathsfX^\backslash mathsfX\backslash boldsymbol$$
The gradient of the loss is:$$\backslash frac=\; \backslash frac=\; 2X^\backslash mathsfY\; +\; 2X^\backslash mathsfX\backslash boldsymbol$$
Setting the gradient of the loss to zero and solving for
\boldsymbol{\beta}
, we get: $$2X^\backslash mathsfY\; +\; 2X^\backslash mathsfX\backslash boldsymbol\; =\; 0\backslash Rightarrow\; X^\backslash mathsfY\; =\; X^\backslash mathsfX\backslash boldsymbol$$$$\backslash boldsymbol\; =\; \backslash left(X^\backslash mathsfX\backslash right)^\; X^\backslash mathsfY$$
Nonlinear least squares
See main article: Nonlinear least squares.
There is, in some cases, a closedform solution to a nonlinear least squares problem – but in general there is not. In the case of no closedform solution, numerical algorithms are used to find the value of the parameters
\beta
that minimizes the objective. Most algorithms involve choosing initial values for the parameters. Then, the parameters are refined iteratively, that is, the values are obtained by successive approximation:$$^\; =\; ^k+\backslash Delta\; \backslash beta\_j,$$where a superscript k is an iteration number, and the vector of increments
\Delta\beta_{j}
is called the shift vector. In some commonly used algorithms, at each iteration the model may be linearized by approximation to a firstorder Taylor series expansion about
\boldsymbol\beta^{k}
:$$\backslash beginf(x\_i,\backslash boldsymbol\; \backslash beta)\; \&=\; f^k(x\_i,\backslash boldsymbol\; \backslash beta)\; +\backslash sum\_j\; \backslash frac\; \backslash left(\backslash beta\_j^k\; \backslash right)\; \backslash \backslash \&=\; f^k(x\_i,\backslash boldsymbol\; \backslash beta)\; +\backslash sum\_j\; J\_\; \backslash ,\backslash Delta\backslash beta\_j.\backslash end$$
The Jacobian J is a function of constants, the independent variable and the parameters, so it changes from one iteration to the next. The residuals are given by$$r\_i\; =\; y\_i\; \; f^k(x\_i,\; \backslash boldsymbol\; \backslash beta)\; \backslash sum\_^\; J\_\backslash ,\backslash Delta\backslash beta\_k\; =\; \backslash Delta\; y\_i\; \backslash sum\_^\; J\_\backslash ,\backslash Delta\backslash beta\_j.$$
To minimize the sum of squares of
r_{i}
, the gradient equation is set to zero and solved for
\Delta\beta_{j}
:$$2\backslash sum\_^n\; J\_\; \backslash left(\backslash Delta\; y\_i\backslash sum\_^m\; J\_\; \backslash ,\; \backslash Delta\; \backslash beta\_k\; \backslash right)\; =\; 0,$$which, on rearrangement, become m simultaneous linear equations, the normal equations:$$\backslash sum\_^\backslash sum\_^m\; J\_\; J\_\; \backslash ,\; \backslash Delta\; \backslash beta\_k=\backslash sum\_^n\; J\_\; \backslash ,\; \backslash Delta\; y\_i\; \backslash qquad\; (j=1,\backslash ldots,m).$$
The normal equations are written in matrix notation as$$\backslash left(\backslash mathbf^\backslash mathsf\; \backslash mathbf\backslash right)\; \backslash Delta\; \backslash boldsymbol\; \backslash beta\; =\; \backslash mathbf^\backslash mathsf\backslash Delta\; \backslash mathbf.$$
These are the defining equations of the Gauss–Newton algorithm.
Differences between linear and nonlinear least squares
 The model function, f, in LLSQ (linear least squares) is a linear combination of parameters of the form
f=X_{i1}\beta_{1}+X_{i2}\beta_{2}+ …
The model may represent a straight line, a parabola or any other linear combination of functions. In NLLSQ (nonlinear least squares) the parameters appear as functions, such as
\beta^{2,}e^{\beta}
and so forth. If the derivatives
\partialf/\partial\beta_{j}
are either constant or depend only on the values of the independent variable, the model is linear in the parameters. Otherwise the model is nonlinear.
 Need initial values for the parameters to find the solution to a NLLSQ problem; LLSQ does not require them.
 Solution algorithms for NLLSQ often require that the Jacobian can be calculated similar to LLSQ. Analytical expressions for the partial derivatives can be complicated. If analytical expressions are impossible to obtain either the partial derivatives must be calculated by numerical approximation or an estimate must be made of the Jacobian, often via finite differences.
 Nonconvergence (failure of the algorithm to find a minimum) is a common phenomenon in NLLSQ.
 LLSQ is globally concave so nonconvergence is not an issue.
 Solving NLLSQ is usually an iterative process which has to be terminated when a convergence criterion is satisfied. LLSQ solutions can be computed using direct methods, although problems with large numbers of parameters are typically solved with iterative methods, such as the Gauss–Seidel method.
 In LLSQ the solution is unique, but in NLLSQ there may be multiple minima in the sum of squares.
 Under the condition that the errors are uncorrelated with the predictor variables, LLSQ yields unbiased estimates, but even under that condition NLLSQ estimates are generally biased.
These differences must be considered whenever the solution to a nonlinear least squares problem is being sought.
Example
Consider a simple example drawn from physics. A spring should obey Hooke's law which states that the extension of a spring is proportional to the force, F, applied to it.
y=f(F,k)=kF
constitutes the model, where F is the independent variable. In order to estimate the force constant, k, we conduct a series of n measurements with different forces to produce a set of data,
(F_{i,}y_{i), i=1,...,n}
, where y_{i} is a measured spring extension.^{[13]} Each experimental observation will contain some error,
\varepsilon
, and so we may specify an empirical model for our observations,
y_{i}=kF_{i}+\varepsilon_{i.}
There are many methods we might use to estimate the unknown parameter k. Since the n equations in the m variables in our data comprise an overdetermined system with one unknown and n equations, we estimate k using least squares. The sum of squares to be minimized is
S=
n  
\sum  
i=1 
(y_{i}
2.  
kF  
i) 
The least squares estimate of the force constant, k, is given by
\hatk=
\sum_{i}F_{i}y_{i}  

.
We assume that applying force causes the spring to expand. After having derived the force constant by least squares fitting, we predict the extension from Hooke's law.
Uncertainty quantification
In a least squares calculation with unit weights, or in linear regression, the variance on the jth parameter,denoted
\operatorname{var}(\hat{\beta}_{j)}
, is usually estimated with
\operatorname{var}(\hat{\beta}_{j)=}\sigma^{2\left(\left[X}^{TX\right]}^{1}\right)_{jj} ≈ \hat{\sigma}^{2}C_{jj},
\hat{\sigma}^{2} ≈
S  
nm 
C=\left(X^{TX\right)}^{1},
where the true error variance σ^{2} is replaced by an estimate, the reduced chisquared statistic, based on the minimized value of the residual sum of squares (objective function), S. The denominator, n−m, is the statistical degrees of freedom; see effective degrees of freedom for generalizations. C is the covariance matrix.
Statistical testing
If the probability distribution of the parameters is known or an asymptotic approximation is made, confidence limits can be found. Similarly, statistical tests on the residuals can be conducted if the probability distribution of the residuals is known or assumed. We can derive the probability distribution of any linear combination of the dependent variables if the probability distribution of experimental errors is known or assumed. Inferring is easy when assuming that the errors follow a normal distribution, consequently implying that the parameter estimates and residuals will also be normally distributed conditional on the values of the independent variables.
It is necessary to make assumptions about the nature of the experimental errors to test the results statistically. A common assumption is that the errors belong to a normal distribution. The central limit theorem supports the idea that this is a good approximation in many cases.
 The Gauss–Markov theorem. In a linear model in which the errors have expectation zero conditional on the independent variables, are uncorrelated and have equal variances, the best linear unbiased estimator of any linear combination of the observations, is its leastsquares estimator. "Best" means that the least squares estimators of the parameters have minimum variance. The assumption of equal variance is valid when the errors all belong to the same distribution.^{[14]}
 If the errors belong to a normal distribution, the leastsquares estimators are also the maximum likelihood estimators in a linear model.
However, suppose the errors are not normally distributed. In that case, a central limit theorem often nonetheless implies that the parameter estimates will be approximately normally distributed so long as the sample is reasonably large. For this reason, given the important property that the error mean is independent of the independent variables, the distribution of the error term is not an important issue in regression analysis. Specifically, it is not typically important whether the error term follows a normal distribution.
Weighted least squares
See main article: Weighted least squares.
A special case of generalized least squares called weighted least squares occurs when all the offdiagonal entries of Ω (the correlation matrix of the residuals) are null; the variances of the observations (along the covariance matrix diagonal) may still be unequal (heteroscedasticity). In simpler terms, heteroscedasticity is when the variance of
Y_{i}
depends on the value of
x_{i}
which causes the residual plot to create a "fanning out" effect towards larger
Y_{i}
values as seen in the residual plot to the right. On the other hand, hom*oscedasticity is assuming that the variance of
Y_{i}
and variance of
U_{i}
are equal.
Relationship to principal components
The first principal component about the mean of a set of points can be represented by that line which most closely approaches the data points (as measured by squared distance of closest approach, i.e. perpendicular to the line). In contrast, linear least squares tries to minimize the distance in the
y
direction only. Thus, although the two use a similar error metric, linear least squares is a method that treats one dimension of the data preferentially, while PCA treats all dimensions equally.
Relationship to measure theory
Notable statistician Sara van de Geer used empirical process theory and the Vapnik–Chervonenkis dimension to prove a leastsquares estimator can be interpreted as a measure on the space of squareintegrable functions.^{[15]}
Regularization
See main article: Regularized least squares.
Tikhonov regularization
In some contexts a regularized version of the least squares solution may be preferable. Tikhonov regularization (or ridge regression) adds a constraint that
2  
\\beta\  
2 
, the squared
\ell_{2}
norm of the parameter vector, is not greater than a given value to the least squares formulation, leading to a constrained minimization problem. This is equivalent to the unconstrained minimization problem where the objective function is the residual sum of squares plus a penalty term
2  
\alpha\\beta\  
2 
and
\alpha
is a tuning parameter (this is the Lagrangian form of the constrained minimization problem).^{[16]}
In a Bayesian context, this is equivalent to placing a zeromean normally distributed prior on the parameter vector.
Lasso method
An alternative regularized version of least squares is Lasso (least absolute shrinkage and selection operator), which uses the constraint that
\\beta\_{1}
, the L1norm of the parameter vector, is no greater than a given value.^{[17]} ^{[18]} ^{[19]} (One can show like above using Lagrange multipliers that this is equivalent to an unconstrained minimization of the leastsquares penalty with
\alpha\\beta\_{1}
added.) In a Bayesian context, this is equivalent to placing a zeromean Laplace prior distribution on the parameter vector.^{[20]} The optimization problem may be solved using quadratic programming or more general convex optimization methods, as well as by specific algorithms such as the least angle regression algorithm.
One of the prime differences between Lasso and ridge regression is that in ridge regression, as the penalty is increased, all parameters are reduced while still remaining nonzero, while in Lasso, increasing the penalty will cause more and more of the parameters to be driven to zero. This is an advantage of Lasso over ridge regression, as driving parameters to zero deselects the features from the regression. Thus, Lasso automatically selects more relevant features and discards the others, whereas Ridge regression never fully discards any features. Some feature selection techniques are developed based on the LASSO including Bolasso which bootstraps samples,^{[21]} and FeaLect which analyzes the regression coefficients corresponding to different values of
\alpha
to score all the features.^{[22]}
The L^{1}regularized formulation is useful in some contexts due to its tendency to prefer solutions where more parameters are zero, which gives solutions that depend on fewer variables.^{[17]} For this reason, the Lasso and its variants are fundamental to the field of compressed sensing. An extension of this approach is elastic net regularization.
See also
 Leastsquares adjustment
 Bayesian MMSE estimator
 Best linear unbiased estimator (BLUE)
 Best linear unbiased prediction (BLUP)
 Gauss–Markov theorem
 L_{2} norm
 Least absolute deviations
 Leastsquares spectral analysis
 Measurement uncertainty
 Orthogonal projection
 Proximal gradient methods for learning
 Quadratic loss function
 Root mean square
 Squared deviations from the mean
Further reading
 Book: Björck, Å. . 9780898713602 . Numerical Methods for Least Squares Problems . SIAM . 1996 .
 Book: T. . Kariya . H. . Kurata . Generalized Least Squares . Hoboken . Wiley . 2004 . 9780470866979 .
 Book: Luenberger, D. G. . David Luenberger . LeastSquares Estimation . Optimization by Vector Space Methods . New York . John Wiley & Sons . 1997 . 1969 . 9780471181170 . 78–102 . https://books.google.com/books?id=lZU0CAH4RccC&pg=PA78 .
 Book: C. R. . Rao . C. R. Rao . H. . Toutenburg . Helge Toutenburg . Linear Models: Least Squares and Alternatives . Springer Series in Statistics . Berlin . Springer . 3rd . 2008 . 9783540742265 . etal.
 Web site: Multidirectional regression analysis . Van de moortel . Koen . April 2021 .
 Book: Wolberg, J. . Data Analysis Using the Method of Least Squares: Extracting the Most Information from Experiments . Berlin . Springer . 2005. 9783540256748.
Notes and References
 Charnes . A. . Frome . E. L. . Yu . P. L. . 10.1080/01621459.1976.10481508 . The Equivalence of Generalized Least Squares and Maximum Likelihood Estimates in the Exponential Family . Journal of the American Statistical Association . 71 . 353 . 169–171 . 1976 .
 Mansfield Merriman, "A List of Writings Relating to the Method of Least Squares"
 Book: Bretscher, Otto . Linear Algebra With Applications . 3rd . Prentice Hall . 1995 . Upper Saddle River, NJ.
 Stephen M. . Stigler . 1981 . Gauss and the Invention of Least Squares . Ann. Stat. . 9 . 3 . 465–474 . 10.1214/aos/1176345451 . free .
 Plackett . R.L. . R. L. Plackett . 1972 . The discovery of the method of least squares . Biometrika . 59 . 2 . 239–251.
 Book: Stigler, Stephen M. . The History of Statistics: The Measurement of Uncertainty Before 1900 . Belknap Press of Harvard University Press . 1986 . Cambridge, MA . 9780674403406 . registration .
 Web site: 20151106 . The Discovery of Statistical Regression . 20230404 . Priceonomics . en.
 10.1111/j.17515823.1998.tb00406.x . J. . Aldrich . 1998. Doing Least Squares: Perspectives from Gauss and Yule . International Statistical Review . 66 . 1 . 61–81. 121471194 .
 Book: A modern introduction to probability and statistics: understanding why and how. 2005. Springer. Dekking, Michel, 1946. 9781852338961. London. 262680588.
 For a good introduction to errorinvariables, please see Book: Fuller, W. A. . Wayne Fuller . Measurement Error Models . John Wiley & Sons . 1987 . 9780471861874 .
 Book: Williams, Jeffrey H. (Jeffrey Huw), 1956. Quantifying measurement: the tyranny of numbers. Morgan & Claypool Publishers, Institute of Physics (Great Britain). 9781681744339. San Rafael [California] (40 Oak Drive, San Rafael, CA, 94903, USA). 962422324. November 2016.
 Book: Rencher. Alvin C.. Methods of Multivariate Analysis. Christensen. William F.. 20120815. John Wiley & Sons. 9781118391679. 155. en.
 Book: Gere, James M.. Mechanics of materials. 2013. Cengage Learning. Goodno, Barry J.. 9781111577735. 8th. Stamford, Conn.. 741541348.
 Book: Hallin . Marc . GaussMarkov Theorem . Wiley,Encyclopedia of Environmetrics . 2012 . 10.1002/9780470057339.vnn102 . 9780471899976 . 18 October 2023.
 van de Geer. Sara. Sara van de Geer. A New Approach to LeastSquares Estimation, with Applications . Annals of Statistics. 15 . 2 . 587–602. June 1987 . 10.1214/aos/1176350362. 123088844 . free.
 van Wieringen . Wessel N. . 2021 . Lecture notes on ridge regression . stat.ME . 1509.09169 .
 Tibshirani . R. . Rob Tibshirani . 1996 . Regression shrinkage and selection via the lasso . Journal of the Royal Statistical Society, Series B . 58. 1 . 267–288 . 2346178.
 Book: The Elements of Statistical Learning . Hastie . Trevor . Tibshirani . Robert . Friedman . Jerome H. . Trevor Hastie . Jerome H. Friedman . second . 2009 . SpringerVerlag . 9780387848587 . dead . https://web.archive.org/web/20091110212529/http://wwwstat.stanford.edu/~tibs/ElemStatLearn/ . 20091110 .
 Book: Bühlmann. Peter. van de Geer. Sara. Sara van de Geer . Statistics for HighDimensional Data: Methods, Theory and Applications. 2011. Springer. 9783642201929.
 Park. Trevor. Casella. George. George Casella. The Bayesian Lasso. Journal of the American Statistical Association. 2008. 103. 482. 681–686. 10.1198/016214508000000337. 11797924.
 Book: Bach. Francis R. Proceedings of the 25th international conference on Machine learning  ICML '08 . Bolasso . 2008. 33–40. 10.1145/1390156.1390161. http://dl.acm.org/citation.cfm?id=1390161. 9781605582054. 2008arXiv0804.1302B. 0804.1302. 609778.
 Zare. Habil. Scoring relevancy of features based on combinatorial analysis of Lasso with application to lymphoma diagnosis. BMC Genomics. 2013. 14. Suppl 1 . S14. 10.1186/1471216414S1S14. 23369194. 3549810 . free .
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