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In statistics, the coefficient of determination, denoted R^{2} or r^{2} and pronounced "R squared", is the proportion of the variance in the dependent variable that is predictable from the independent variable(s).
It is a statistic used in the context of statistical models whose main purpose is either the prediction of future outcomes or the testing of hypotheses, on the basis of other related information. It provides a measure of how well observed outcomes are replicated by the model, based on the proportion of total variation of outcomes explained by the model.^{[1]}^{[2]}^{[3]}
There are several definitions of R^{2} that are only sometimes equivalent. One class of such cases includes that of simple linear regression where r^{2} is used instead of R^{2}. When an intercept is included, then r^{2} is simply the square of the sample correlation coefficient (i.e., r) between the observed outcomes and the observed predictor values.^{[4]} If additional regressors are included, R^{2} is the square of the coefficient of multiple correlation. In both such cases, the coefficient of determination normally ranges from 0 to 1.
There are cases where the computational definition of R^{2} can yield negative values, depending on the definition used. This can arise when the predictions that are being compared to the corresponding outcomes have not been derived from a modelfitting procedure using those data. Even if a modelfitting procedure has been used, R^{2} may still be negative, for example when linear regression is conducted without including an intercept,^{[5]} or when a nonlinear function is used to fit the data.^{[6]} In cases where negative values arise, the mean of the data provides a better fit to the outcomes than do the fitted function values, according to this particular criterion. Since the most general definition of the coefficient of determination is also known as the Nash–Sutcliffe model efficiency coefficient, this last notation is preferred in many fields, because denoting a goodnessoffit indicator that can vary from −∞ to 1 (i.e., it can yield negative values) with a squared letter is confusing.
When evaluating the goodnessoffit of simulated (Y_{pred}) vs. measured (Y_{obs}) values, it is not appropriate to base this on the R^{2} of the linear regression (i.e., Y_{obs}= m·Y_{pred} + b). The R^{2} quantifies the degree of any linear correlation between Y_{obs} and Y_{pred}, while for the goodnessoffit evaluation only one specific linear correlation should be taken into consideration: Y_{obs} = 1·Y_{pred} + 0 (i.e., the 1:1 line).^{[7]}^{[8]}
Definitions
A data set has n values marked y_{1},...,y_{n} (collectively known as y_{i} or as a vector y = [y_{1},...,y_{n}]^{T}), each associated with a fitted (or modeled, or predicted) value f_{1},...,f_{n} (known as f_{i}, or sometimes ŷ_{i}, as a vector f).
Define the residuals as e_{i} = y_{i} − f_{i} (forming a vector e).
If is the mean of the observed data:
then the variability of the data set can be measured with two sums of squares formulas:
 The total sum of squares (proportional to the variance of the data):
 The sum of squares of residuals, also called the residual sum of squares:
The most general definition of the coefficient of determination is
In the best case, the modeled values exactly match the observed values, which results in and . A baseline model, which always predicts , will have . Models that have worse predictions than this baseline will have a negative .
Relation to unexplained variance
In a general form, R^{2} can be seen to be related to the fraction of variance unexplained (FVU), since the second term compares the unexplained variance (variance of the model's errors) with the total variance (of the data):
As explained variance
Suppose R^{2} = 0.49. This implies that 49% of the variability of the dependent variable has been accounted for, and the remaining 51% of the variability is still unaccounted for. In some cases the total sum of squares equals the sum of the two other sums of squares defined above,
If the regression sum of squares, also called the explained sum of squares, is given by:
then
See Partitioning in the general OLS model for a derivation of this result for one case where the relation holds. When this relation does hold, the above definition of R^{2} is equivalent to
where n is the number of observations (cases) on the variables.
In this form R^{2} is expressed as the ratio of the explained variance (variance of the model's predictions, which is SS_{reg} / n) to the total variance (sample variance of the dependent variable, which is SS_{tot} / n).
This partition of the sum of squares holds for instance when the model values ƒ_{i} have been obtained by linear regression. A milder sufficient condition reads as follows: The model has the form
where the q_{i} are arbitrary values that may or may not depend on i or on other free parameters (the common choice q_{i} = x_{i} is just one special case), and the coefficient estimates and are obtained by minimizing the residual sum of squares.
This set of conditions is an important one and it has a number of implications for the properties of the fitted residuals and the modelled values. In particular, under these conditions:
As squared correlation coefficient
In linear least squares multiple regression with an estimated intercept term, R^{2} equals the square of the Pearson correlation coefficient between the observed and modeled (predicted) data values of the dependent variable.
In a linear least squares regression with an intercept term and a single explanator, this is also equal to the squared Pearson correlation coefficient of the dependent variable and explanatory variable
It should not be confused with the correlation coefficient between two estimates, defined as
where the covariance between two coefficient estimates, as well as their standard deviations, are obtained from the covariance matrix of the coefficient estimates.
Under more general modeling conditions, where the predicted values might be generated from a model different from linear least squares regression, an R^{2} value can be calculated as the square of the correlation coefficient between the original and modeled data values. In this case, the value is not directly a measure of how good the modeled values are, but rather a measure of how good a predictor might be constructed from the modeled values (by creating a revised predictor of the form α + βƒ_{i}).^{[citation needed]} According to Everitt (p. 78),^{[9]} this usage is specifically the definition of the term "coefficient of determination": the square of the correlation between two (general) variables.
Interpretation
R^{2} is a statistic that will give some information about the goodness of fit of a model. In regression, the R^{2} coefficient of determination is a statistical measure of how well the regression predictions approximate the real data points. An R^{2} of 1 indicates that the regression predictions perfectly fit the data.
Values of R^{2} outside the range 0 to 1 can occur when the model fits the data worse than a horizontal hyperplane. This would occur when the wrong model was chosen, or nonsensical constraints were applied by mistake. If equation 1 of Kvålseth^{[10]} is used (this is the equation used most often), R^{2} can be less than zero. If equation 2 of Kvålseth is used, R^{2} can be greater than one.
In all instances where R^{2} is used, the predictors are calculated by ordinary leastsquares regression: that is, by minimizing SS_{res}. In this case, R^{2} increases as the number of variables in the model is increased (R^{2} is monotone increasing with the number of variables included—it will never decrease). This illustrates a drawback to one possible use of R^{2}, where one might keep adding variables (Kitchen sink regression) to increase the R^{2} value. For example, if one is trying to predict the sales of a model of car from the car's gas mileage, price, and engine power, one can include such irrelevant factors as the first letter of the model's name or the height of the lead engineer designing the car because the R^{2} will never decrease as variables are added and will probably experience an increase due to chance alone.
This leads to the alternative approach of looking at the adjusted R^{2}. The explanation of this statistic is almost the same as R^{2} but it penalizes the statistic as extra variables are included in the model. For cases other than fitting by ordinary least squares, the R^{2} statistic can be calculated as above and may still be a useful measure. If fitting is by weighted least squares or generalized least squares, alternative versions of R^{2} can be calculated appropriate to those statistical frameworks, while the "raw" R^{2} may still be useful if it is more easily interpreted. Values for R^{2} can be calculated for any type of predictive model, which need not have a statistical basis.
In a multivariate linear model
Consider a linear model with more than a single explanatory variable, of the form
where, for the ith case, is the response variable, are p regressors, and is a mean zero error term. The quantities are unknown coefficients, whose values are estimated by least squares. The coefficient of determination R^{2} is a measure of the global fit of the model. Specifically, R^{2} is an element of [0, 1] and represents the proportion of variability in Y_{i} that may be attributed to some linear combination of the regressors (explanatory variables) in X.^{[11]}
R^{2} is often interpreted as the proportion of response variation "explained" by the regressors in the model. Thus, R^{2} = 1 indicates that the fitted model explains all variability in , while R^{2} = 0 indicates no 'linear' relationship (for straight line regression, this means that the straight line model is a constant line (slope = 0, intercept = ) between the response variable and regressors). An interior value such as R^{2} = 0.7 may be interpreted as follows: "Seventy percent of the variance in the response variable can be explained by the explanatory variables. The remaining thirty percent can be attributed to unknown, lurking variables or inherent variability."
A caution that applies to R^{2}, as to other statistical descriptions of correlation and association is that "correlation does not imply causation." In other words, while correlations may sometimes provide valuable clues in uncovering causal relationships among variables, a nonzero estimated correlation between two variables is not, on its own, evidence that changing the value of one variable would result in changes in the values of other variables. For example, the practice of carrying matches (or a lighter) is correlated with incidence of lung cancer, but carrying matches does not cause cancer (in the standard sense of "cause").
In case of a single regressor, fitted by least squares, R^{2} is the square of the Pearson productmoment correlation coefficient relating the regressor and the response variable. More generally, R^{2} is the square of the correlation between the constructed predictor and the response variable. With more than one regressor, the R^{2} can be referred to as the coefficient of multiple determination.
Inflation of R^{2}
In least squares regression using typical data, R^{2} is at least weakly increasing with increases in the number of regressors in the model. Because increases in the number of regressors increase the value of R^{2}, R^{2} alone cannot be used as a meaningful comparison of models with very different numbers of independent variables. For a meaningful comparison between two models, an Ftest can be performed on the residual sum of squares, similar to the Ftests in Granger causality, though this is not always appropriate. As a reminder of this, some authors denote R^{2} by R_{q}^{2}, where q is the number of columns in X (the number of explanators including the constant).
To demonstrate this property, first recall that the objective of least squares linear regression is
where X_{i} is a row vector of values of explanatory variables for case i and b is a column vector of coefficients of the respective elements of X_{i}.
The optimal value of the objective is weakly smaller as more explanatory variables are added and hence additional columns of (the explanatory data matrix whose ith row is X_{i}) are added, by the fact that less constrained minimization leads to an optimal cost which is weakly smaller than more constrained minimization does. Given the previous conclusion and noting that depends only on y, the nondecreasing property of R^{2} follows directly from the definition above.
The intuitive reason that using an additional explanatory variable cannot lower the R^{2} is this: Minimizing is equivalent to maximizing R^{2}. When the extra variable is included, the data always have the option of giving it an estimated coefficient of zero, leaving the predicted values and the R^{2} unchanged. The only way that the optimization problem will give a nonzero coefficient is if doing so improves the R^{2}.
Caveats
R^{2} does not indicate whether:
 the independent variables are a cause of the changes in the dependent variable;
 omittedvariable bias exists;
 the correct regression was used;
 the most appropriate set of independent variables has been chosen;
 there is collinearity present in the data on the explanatory variables;
 the model might be improved by using transformed versions of the existing set of independent variables;
 there are enough data points to make a solid conclusion.
Extensions
Adjusted R^{2}
The use of an adjusted R^{2} (one common notation is , pronounced "R bar squared"; another is ) is an attempt to account for the phenomenon of the R^{2} automatically and spuriously increasing when extra explanatory variables are added to the model. Originated by Henri Theil, it is a modification of R^{2} that adjusts for the number of explanatory terms in a model () relative to the number of data points ().^{[12]} The adjusted R^{2} is defined as
where p is the total number of explanatory variables in the model (not including the constant term), and n is the sample size. It can also be written as:
where df_{t} is the degrees of freedom n – 1 of the estimate of the population variance of the dependent variable, and df_{e} is the degrees of freedom n – p – 1 of the estimate of the underlying population error variance.
The adjusted R^{2} can be negative, and its value will always be less than or equal to that of R^{2}. Unlike R^{2}, the adjusted R^{2} increases only when the increase in R^{2} (due to the inclusion of a new explanatory variable) is more than one would expect to see by chance. If a set of explanatory variables with a predetermined hierarchy of importance are introduced into a regression one at a time, with the adjusted R^{2} computed each time, the level at which adjusted R^{2} reaches a maximum, and decreases afterward, would be the regression with the ideal combination of having the best fit without excess/unnecessary terms.
Adjusted R^{2} can be interpreted as an unbiased (or less biased) estimator of the population R^{2}, whereas the observed sample R^{2} is a positively biased estimate of the population value.^{[13]} Adjusted R^{2} is more appropriate when evaluating model fit (the variance in the dependent variable accounted for by the independent variables) and in comparing alternative models in the feature selection stage of model building.^{[13]}
The principle behind the adjusted R^{2} statistic can be seen by rewriting the ordinary R^{2} as
where and are the sample variances of the estimated residuals and the dependent variable respectively, which can be seen as biased estimates of the population variances of the errors and of the dependent variable. These estimates are replaced by statistically unbiased versions: and .
Coefficient of partial determination
The coefficient of partial determination can be defined as the proportion of variation that cannot be explained in a reduced model, but can be explained by the predictors specified in a full(er) model.^{[14]}^{[15]}^{[16]} This coefficient is used to provide insight into whether or not one or more additional predictors may be useful in a more fully specified regression model.
The calculation for the partial R^{2} is relatively straightforward after estimating two models and generating the ANOVA tables for them. The calculation for the partial R^{2} is
which is analogous to the usual coefficient of determination:
Generalizing and decomposing R^{2} ^{[17]}
As explained above, model selection heuristics such as the Adjusted criterion and the Ftest examine whether the total sufficiently increases to determine if a new regressor should be added to the model. If a regressor is added to the model that is highly correlated with other regressors which have already been included, then the total will hardly increase, even if the new regressor is of relevance. As a result, the abovementioned heuristics will ignore relevant regressors when crosscorrelations are high.
Alternatively, one can decompose a generalized version of to quantify the relevance of deviating from a hypothesis.^{[17]} As Hoornweg (2018) shows, several shrinkage estimators – such as Bayesian linear regression, ridge regression, and the (adaptive) lasso – make use of this decomposition of when they gradually shrink parameters from the unrestricted OLS solutions towards the hypothesized values. Let us first define the linear regression model as
It is assumed that the matrix is standardized with Zscores and that the column vector is centered to have a mean of zero. Let the column vector refer to the hypothesized regression parameters and let the column vector denote the estimated parameters. We can then define
An of 75% means that the insample accuracy improves by 75% if the dataoptimized solutions are used instead of the hypothesized values. In the special case that is a vector of zeros, we obtain the traditional again.
The individual effect on of deviating from a hypothesis can be computed with ('Router'). This times matrix is given by
where . The diagonal elements of exactly add up to . If regressors are uncorrelated and is a vector of zeros, then the diagonal element of simply corresponds to the value between and . When regressors and are correlated, might increase at the cost of a decrease in . As a result, the diagonal elements of may be smaller than 0 and, in more exceptional cases, larger than 1. To deal with such uncertainties, several shrinkage estimators implicitly take a weighted average of the diagonal elements of to quantify the relevance of deviating from a hypothesized value.^{[17]} Click on the lasso for an example.
R^{2} in logistic regression
In the case of logistic regression, usually fit by maximum likelihood, there are several choices of pseudoR^{2}.
One is the generalized R^{2} originally proposed by Cox & Snell,^{[18]} and independently by Magee:^{[19]}
where is the likelihood of the model with only the intercept, is the likelihood of the estimated model (i.e., the model with a given set of parameter estimates) and n is the sample size. It is easily rewritten to:
where D is the test statistic of the likelihood ratio test.
Nagelkerke^{[20]} noted that it had the following properties:
 It is consistent with the classical coefficient of determination when both can be computed;
 Its value is maximised by the maximum likelihood estimation of a model;
 It is asymptotically independent of the sample size;
 The interpretation is the proportion of the variation explained by the model;
 The values are between 0 and 1, with 0 denoting that model does not explain any variation and 1 denoting that it perfectly explains the observed variation;
 It does not have any unit.
However, in the case of a logistic model, where cannot be greater than 1, R^{2} is between 0 and : thus, Nagelkerke suggested the possibility to define a scaled R^{2} as R^{2}/R^{2}_{max}.^{[21]}
Comparison with norm of residuals
Occasionally, the norm of residuals is used for indicating goodness of fit. This term is calculated as the squareroot of the sum of squares of residuals:
Both R^{2} and the norm of residuals have their relative merits. For least squares analysis R^{2} varies between 0 and 1, with larger numbers indicating better fits and 1 representing a perfect fit. The norm of residuals varies from 0 to infinity with smaller numbers indicating better fits and zero indicating a perfect fit. One advantage and disadvantage of R^{2} is the term acts to normalize the value. If the y_{i} values are all multiplied by a constant, the norm of residuals will also change by that constant but R^{2} will stay the same. As a basic example, for the linear least squares fit to the set of data:
R^{2} = 0.998, and norm of residuals = 0.302. If all values of y are multiplied by 1000 (for example, in an SI prefix change), then R^{2} remains the same, but norm of residuals = 302.
Another singleparameter indicator of fit is the RMSE of the residuals, or standard deviation of the residuals. This would have a value of 0.135 for the above example given that the fit was linear with an unforced intercept.^{[22]}
History
The creation of the coefficient of determination has been attributed to the geneticist Sewall Wright and was first published in 1921.^{[23]}
See also
 Anscombe's quartet
 Fraction of variance unexplained
 Goodness of fit
 Nash–Sutcliffe model efficiency coefficient (hydrological applications)
 Pearson productmoment correlation coefficient
 Proportional reduction in loss
 Regression model validation
 Root mean square deviation
 Stepwise regression
 ttest of
Notes
 ^ Steel, R. G. D.; Torrie, J. H. (1960). Principles and Procedures of Statistics with Special Reference to the Biological Sciences. McGraw Hill.
 ^ Glantz, Stanton A.; Slinker, B. K. (1990). Primer of Applied Regression and Analysis of Variance. McGrawHill. ISBN 9780070234079.
 ^ Draper, N. R.; Smith, H. (1998). Applied Regression Analysis. WileyInterscience. ISBN 9780471170822.
 ^ Devore, Jay L. (2011). Probability and Statistics for Engineering and the Sciences (8th ed.). Boston, MA: Cengage Learning. pp. 508–510. ISBN 9780538733526.
 ^ Barten, Anton P. (1987). "The Coeffecient of Determination for Regression without a Constant Term". In Heijmans, Risto; Neudecker, Heinz (eds.). The Practice of Econometrics. Dordrecht: Kluwer. pp. 181–189. ISBN 9024735025.
 ^ Colin Cameron, A.; Windmeijer, Frank A.G. (1997). "An Rsquared measure of goodness of fit for some common nonlinear regression models". Journal of Econometrics. 77 (2): 1790–2. doi:10.1016/S03044076(96)018180.
 ^ Legates, D.R.; McCabe, G.J. (1999). "Evaluating the use of "goodnessoffit" measures in hydrologic and hydroclimatic model validation". Water Resour. Res. 35 (1): 233–241. doi:10.1029/1998WR900018.
 ^ Ritter, A.; MuñozCarpena, R. (2013). "Performance evaluation of hydrological models: statistical significance for reducing subjectivity in goodnessoffit assessments". Journal of Hydrology. 480 (1): 33–45. doi:10.1016/j.jhydrol.2012.12.004.
 ^ Everitt, B. S. (2002). Cambridge Dictionary of Statistics (2nd ed.). CUP. ISBN 9780521810999.
 ^ Kvalseth, Tarald O. (1985). "Cautionary Note about R2". The American Statistician. 39 (4): 279–285. doi:10.2307/2683704. JSTOR 2683704.
 ^ Computing Adjusted R2 for Polynomial Regressions
 ^ Theil, Henri (1961). Economic Forecasts and Policy. Holland, Amsterdam: North. p. 213.
 ^ ^{a} ^{b} Shieh, Gwowen (20080401). "Improved shrinkage estimation of squared multiple correlation coefficient and squared crossvalidity coefficient". Organizational Research Methods. 11 (2): 387–407. doi:10.1177/1094428106292901. ISSN 10944281. S2CID 55098407.
 ^ Richard AndersonSprecher, "Model Comparisons and R^{2}", The American Statistician, Volume 48, Issue 2, 1994, pp. 113–117.
 ^ (generalized to Maximum Likelihood) N. J. D. Nagelkerke, "A Note on a General Definition of the Coefficient of Determination", Biometrika, Vol. 78, No. 3. (Sep., 1991), pp. 691–692.
 ^ "R implementation of coefficient of partial determination"
 ^ ^{a} ^{b} ^{c} Hoornweg, Victor (2018). "Part II: On Keeping Parameters Fixed". Science: Under Submission. Hoornweg Press. ISBN 9789082918809.
 ^ Cox, D. D.; Snell, E. J. (1989). The Analysis of Binary Data (2nd ed.). Chapman and Hall.
 ^ Magee, L. (1990). "R^{2} measures based on Wald and likelihood ratio joint significance tests". The American Statistician. 44. pp. 250–3. doi:10.1080/00031305.1990.10475731.
 ^ Nagelkerke, Nico J. D. (1992). Maximum Likelihood Estimation of Functional Relationships, PaysBas. Lecture Notes in Statistics. 69. ISBN 9780387977218.
 ^ Nagelkerke, N. J. D. (1991). "A Note on a General Definition of the Coefficient of Determination". Biometrika. 78 (3): 691–2. doi:10.1093/biomet/78.3.691. JSTOR 2337038.
 ^ OriginLab webpage, http://www.originlab.com/doc/OriginHelp/LRAlgorithm. Retrieved February 9, 2016.
 ^ Wright, Sewell (January 1921). "Correlation and causation". Journal of Agricultural Research. 20: 557–585.
Further reading
 Gujarati, Damodar N.; Porter, Dawn C. (2009). Basic Econometrics (Fifth ed.). New York: McGrawHill/Irwin. pp. 73–78. ISBN 9780073375779.
 Hughes, Ann; Grawoig, Dennis (1971). Statistics: A Foundation for Analysis. Reading: AddisonWesley. pp. 344–348. ISBN 0201030217.
 Kmenta, Jan (1986). Elements of Econometrics (Second ed.). New York: Macmillan. pp. 240–243. ISBN 9780023650703.
 LewisBeck, Michael S.; Skalaban, Andrew (1990). "The RSquared: Some Straight Talk". Political Analysis. 2: 153–171. doi:10.1093/pan/2.1.153. JSTOR 23317769.