1. Introduction
Capital Asset Pricing Model (CAPM) was discovered by Sharpe (1964) which showed correlation between the market risk premium and a stock return. CAPM have been improved and many of research have been carried out to verify it. Later, Fama & French (1993) developed the Fama - French three factor model (FF3 model) from CAPM by adding size, and book to market ratio. Therefore, FF3 model is a very significant part in analysis. Shaharuddin, Lau, & Ahmad (2018) also used the FF3 model and found the FF3 model is valid for Islamic unit trust funds before and after the collapse of Lehman Brothers. In addition, Asmarani & Wijaya (2020) found the market risk premium and value risk premium are significant positive relationship on retail banks stock return listed in Indonesia Stock Exchange. Later, Fama & French (2015) proposed including profitability and investment to create the Fama - French five factor models (FF5 model) as the following equation,
\(\begin{aligned} R_{i t}-R f_{t}=& a_{i}+b_{i}(R m-R f)_{t}+s_{i} S M B_{t}+h_{i} H M L_{t} \\ &+r_{i} R M W_{t}+c_{i} C M A_{t} \end{aligned}\) (1)
where Ri is the return of portfolio i, Rf is the risk-free rate, Rm is return of the market portfolio, SMB is small minus big, HML is high minus low, RMW is robust minus weak, and CMA is conservative minus aggressive.
Although the CAPM, FF3 model, and FF5 model are popular and effective for explain and predicting the stock returns but those models are time-invariant parameters. Hence, the analysis does not come close to the fact that each factor has a different effect over time. For the publication about the time-varying coefficient, Hongsakulvasu & Liammukda (2020) had studied the time-varying coefficient autoregressive model by using a generalized additive model with thin-plate spline to predict 4 Asian stock price index, from a result of this study, the coefficients of the models were varied over time. Therefore, it is interesting to know if we can use the time-varying coefficient on the FF5 model.
2. Statistical Theory and Literature Review
2.1. Time-Varying Coefficient with the Generalized Additive Model
For the time-varying coefficient model, it assumed one time-varying coefficient (ct ) for the model to be estimated in equation (2) and using regression splines method to estimate the time-varying coefficient as the following equation (3).
rt = ct + εt (2)
\(\hat{c}_{t}=\hat{\alpha}_{1} R_{1}(t)+\hat{\alpha}_{2} R_{2}(t)+\hat{\alpha}_{3} R_{3}(t)+\ldots .+\hat{\alpha}_{K} R_{K}(t);\) (3)
where we have estimation\(\hat{c}_{t}\) with term of K basis function R1 (t), …, Rk (t) and t represent the time, then \(\hat{c}_{t}\) can be estimated by using a linear regression method. For shape of \(\hat{c}\) , It can be either linear or non-linear shape which is dependent on time. In practice, \(\hat{c}_{t}\) has many approaches on the type of basis function such as a cubic regression splines and thin-plate regression splines. One can call this method as a data driven approach, since each basis function can be calculated from the data (Bringmann et al., 2017; Hongsakulvasu & Liammukda, 2020).
2.2. Thin Plate Regression Splines
yi = g(xi ) + εi (4)
where εi is a random residual of estimation. Function g can smoothen estimates with thin-plate spline by optimization base on function g minimizing.
\(\sum_{i=1}^{n}\|\mathbf{y}-\mathbf{g}\|^{2}+\lambda J_{m d}(g)\) (5)
where y is the vector of yt , g = (g(x1 ),…, g(xn ))′, λ is a parameter that represents a trade-off between smoothness and fitting of g, Jmd (g) is a penalty functional measuring the wiggliness of g. Jmd (g)which is defined as:
\(J_{m d}=\int \ldots \int_{\mathbb{R}^{d}} \sum_{v_{t}+\ldots+v_{t}=m} \frac{m !}{v_{1} ! \ldots v_{d} !}\left(\frac{\partial^{m} g}{\partial x_{1}^{v_{1}} \ldots \partial x_{d}^{v_{d}}}\right)^{2} d x_{1} \ldots d x_{d}\) (6)
The analysis has a one technical restriction is 2m > d, it can be shown that the function minimizing expression (5) has the form
\(g(\mathrm{x})=\sum_{i=1}^{n} \delta_{i} \eta_{m d}\left(\left\|\mathbf{x}-\mathbf{x}_{i}\right\|\right)+\sum_{j=1}^{M} \alpha_{j} \phi_{j}(\mathrm{x})\) (7)
where δ and α are unknown parameter vectors under condition that \(T_{\mathrm{ij}}=\varphi_{\mathrm{j}}(x i)\)and. \(\mathrm{T}^{\prime} \delta=0\).The \(M=\left(\begin{array}{c} m+d-1 \\ d \end{array}\right)\) functions φi are linearly independent polynomials spanning the space of polynomials \(\mathbb{R}^{d}\) in d of degree less than m (wood, 2006).
\(\begin{array}{l} \eta_{m d}(r)= \\ \quad\left\{\begin{array}{l} \frac{(-1)^{m+1+d / 2}}{2^{2 m-1} \pi^{d / 2}(m-1) !(m-d / 2) !} r^{2 m-d} \log (r) d \text { event } \\ \frac{\Gamma(d / 2-m)}{2^{2 m-1} \pi^{d / 2}(m-1) !} r^{2 m-d} \end{array} \quad d\right. \text { odd } \end{array}\) (8)
Next, defining matrix E by \(E_{i j} \equiv \eta_{m d}\left(\left\|x-x_{i}\right\|\right)\) , the thinplate spline fitting problem are defined as the following equation:
\(\text { Minimize }\|\mathbf{y}-E \delta-T \alpha\|^{2}+\lambda \delta^{\prime} E \delta \text { Subject to } \mathrm{T}^{\prime} \delta=0\) (9)
With respect to δ and α. The function g estimated with system of equation (9) is something of an ideal smoother because it considered the smoothness of the system of equations by using λ to weight a penalty functional Jmd (g).
The last, estimate an optimal smoothing parameter λ and the number of basis dimensions. This can be done in generalized additive model by Generalized Cross Validation score (GCV). It minimizes as the following equation:
\(G C V=\frac{T \sum_{t=1}^{T}\left(y_{t}-\hat{y}_{t}\right)^{2}}{[t r(I-A)]^{2}}\) (10)
where A is the projection matrix. If a value of smoothing parameter λ is close to 1 then spline will be over-smoothed, On the opposite side, when value of smoothing parameter λ is close to zero than spline isn’t penalized, so the method behaves like a classical ordinary least squares (OLS). With a number of basis dimensions of Estimated Degrees of Freedom (EDF), it is opposite. Higher EDF refers to that fit will be overfit (less smoothed), on the other side lower EDF refers to more smoothed behavior of fitted values (Wahba, 1980; Wood, 2006).
2.3. Augmented Dickey-Fuller test
An augmented Dickey-Fuller test apply for the testing of a complicated sets of time series models, the disturbances of the Augmented Dickey-Fuller test require to be white noise, however whether the disturbances of the model have some forms of serial correlation, the stationary will be executed by ADF Unit Root Test. The descriptive equation as follows:
\(y_{t}=c_{t}+\gamma y_{t-1} \sum_{i=1}^{p} \phi_{i} \Delta y_{t-i}+e_{t}\) (12)
where ct is a deterministic function of time index and it can be divided into three type as the flowing, there is no intercept term, then ct = 0, there is intercept term, then ct = constant, and there is intercept and trend, then ct = µ + βt .
Therefore, the null and alternative hypothesis can be written as, H0 : γ = 1 for non-stationary (there is unit root in time series data) and H1 : γ < 1 for stationary. According to the first differencing the above equation by deduction yt−1 on both side, then we get the following equation;
\(\Delta y_{t}=c_{t}+\gamma_{c} y_{t-1} \sum_{i=1}^{p-1} \phi_{i} \Delta y_{t-i}+e_{t};\) (13)
where γc = γ − 1. After first differencing equation (13), the null and alternative hypothesis are H0 : γc = 0 for nonstationary and H1 : γc < 0 for stationary. The ADF test statistic is defined as
\(A D F=\frac{\hat{\gamma}-1}{\operatorname{std}(\hat{\gamma})}\) (14)
where \(\hat{\gamma}\) is the coefficient estimation and std (\(\hat{\gamma}\)) is its corresponding estimation of standard error for each type of linear model. The p-value is calculated by interpolating the test statistics from the corresponding critical values tables.
2.4. Literature Review
After Fama & French proposed FF5 model by adding RMW and CMA factors on FF3 model, many researchers examined this model and used it to explain a return of portfolios. We can conclude publication about FF5 model as the following
Sundqvist (2017) studied average returns in the Nordic markets during the period from December 1997 to June 2016 by using CAPM, FF3 model, and FF5 model. They can explain the average returns of portfolios sorted on size and book-to-market ratio, and portfolios sorted on size and investment, but it is not happening for portfolios sorted on size and profitability. While the FF5 model provides a more mean-variance efficient portfolio from its explanatory variables which is close to a study by Huang (2019), He compared the CAPM, FF3 model, Carhart4, and FF5 model in explaining individual stock returns in China from January 1994 to December 2016. RMW and CMA factors were significant and the FF5 model was the highest performing compared to other traditional asset pricing models in explaining individual stock returns in China. In addition, Mosoeu & Kodongo (2019) used a Generalized Method of Moments (GMM) for estimating parameters in the FF5model and used average stock returns for emerging and selected developed equity markets from January 2010 to December 2015. From the result, RMW was found to be most effective for explaining average equity returns in emerging markets.
But the results of many researchers’ studies are not the same as those of the above studies. Nguyen (2016) studied the average return of stock in Vietnam stock exchange for the period of January 2011 to December 2015 by using CAPM, FF3 model, and FF5 model. The result of this study shows that from CAPM to FF5 model, the R-square increases gradually and FF5 model has the highest R-square, but it was only 34 percent and RMW and CMA proved insignificant in explaining the stock returns. Which is close to the study by Kubota and Takehara (2018), They investigated the FF5 model for explaining return of stocks in Tokyo Stock Exchange (TSE) from January 1978 to December 2014, they used a Generalized Method of Moments (GMM) for estimating parameter in FF5 model. From the result, they found that RMW and CMA are insignificant in explaining return from stocks. Thus, they concluded that the original version of the FF5 model was not the best benchmark pricing model for the Japanese. In addition, Wijaya, Irawan, & Mahadwartha (2018) explained the stocks listed in the LQ45 Index since January 2013 to December 2015 by using FF5 model. Rm-Rf, HML, and CMA had a positively significant effect on return and SMB had negatively significant effect on return, but RMW was insignificant.
On the other hand, some researchers developed FF5 model to increase the performance of this model. Chiah, Chai, Zhong, & Li (2016) investigated the performance of FF5 model in pricing Australian equities since January 1982 to December 2013. They found that the FF5 model can explain more asset pricing anomalies than a range of competing asset pricing models, which supports the superiority of the FF5 model. Moreover, they can capture the volatility of equities by used the GARCH model. Furthermore, de la O González & Jareño (2019) studied U.S. sector returns from November 1989 to February 2014 by using the FF5 model base on Quantile linear regression. From the result, the extreme value at quantile 0.1 of the return distribution has the best results. In addition, Jan & Ayub (2019) forecasted the stock returns in the emerging markets by using the FF5 model with Artificial Neural Networks (ANN). Their study reinforces the financial concept that says “high risk - high return” and the FF5 model base on ANN will significantly improve the return on investments.
From the literature review, every publication used the FF5 model base on a multiple linear regression model with time-invariant parameters, so those models cannot capture and show a different effect at different times for the 5 factors. By this point, it is interesting to study that we can capture and show a different effect at different times for 5 factors or not?
3. Research Methods and Materials
3.1. Scope of the Study and Data Used
This study was conducted by using monthly data set from Kenneth R. French home page mba.tuck.dartmouth.edu/ pages/faculty/ken.french/. The data starts from July 1990 to April 2020, the details are as follows:
1. Japan portfolios are weight return of stocks in Tokyo Stock Exchange (TSE) which is sorted on size and book-to-market ratio. The portfolios are the intersections of 2 portfolios formed on size (market equity, ME) and 3 portfolios formed on the ratio of book equity to market equity (BE/ME). The size breakpoint for year t is the median TSE market equity at the end of June of year t. The BE/ ME breakpoints are the 30th and 70th TSE percentiles (see Table 1).
Table 1: Japan portfolios
2. Return of risk-free rate (Rf) is Return on a 1-Month Treasury Bill (short-term U.S. government debt obligation).
3. Return of the market portfolio (Rm) is value-weight return of firms in the Tokyo Stock Exchange.
4. Fama - French 5 Factor are internal factor including Market Risk Premium, Small Minus Big, High Minus Low, Robust Minus Weak, and Conservative Minus Aggressive with details as follows:
Market Risk Premium (Rm-Rf) describes the relationship between returns from an equity market portfolio and treasury bond yields. It reflects required returns, historical returns, and expected returns. The historical market risk premium will be the same for all investors since the value is based on what has happened. It can be calculated by using the return of the market portfolio minus the return of the market portfolio.
Small Minus Big (SMB) reflects a size risk premium, It can be calculated by using the average return on the nine small stock portfolios minus the average return on the nine big stock portfolios.
High Minus Low (HML) reflects a value risk premium, It can be calculated by using the average return on the two value portfolios minus the average return on the two growth portfolios.
Robust Minus Weak (RMW) reflects an profitability risk premium, It can be calculated by using the average return on the two robust operating profitability portfolios minus the average return on the two weak operating profitability portfolios (operating profit is profits from a core business function of company).
Conservative Minus Aggressive (CMA) reflects an investment risk premium, It can be calculated by using the average return on the two conservative investment portfolios minus the average return on the two aggressive investment portfolios.
3.2. Empirical Methods
For the first analysis of the time-series data, we must check stationary conditions on an endogenous and exogenous variable by using the Augmented Dickey-Fuller test (ADF test) with 3 equations including no intercept, Intercept, and intercept & trend because if data is nonstationary, it maybe spurious regression.
For the next analysis, we use time-varying coefficient Fama - French five factor model (TV-FF5 model) to explain the return of Japan portfolios as the following equation:
\(\begin{aligned} R_{\mathrm{it}}-R f_{\mathrm{t}}=&\left.a_{\mathrm{it}}+b_{\mathrm{it}}(R m-R f)_{\mathrm{t}}+s_{\mathrm{it}} S M B_{\mathrm{t}}+h_{\mathrm{it}} H M L_{\mathrm{t}}+r_{\mathrm{it}} R M W_{\mathrm{t}}\right) \\ &+c_{\mathrm{it}} C M A_{\mathrm{t}}+\varepsilon_{\mathrm{t}}; \end{aligned}\) (18)
where the time-varying coefficient\(\hat{a}_{i t}, \hat{b}_{i t}, \hat{s}_{i t}, \hat{h}_{i t}, \hat{r}_{i t}\), and \(\hat{c}_{i t}\) can be estimated by using generalized additive model with thin-plate spline as the following equation:
\(\hat{g}_{t}=\hat{\gamma}_{1} T P_{1}(t)+\hat{\gamma}_{2} T P_{2}(t)+\hat{\gamma}_{3} T P_{3}(t)+\ldots+\hat{\gamma}_{K} T P_{K}(t);\) (19)
where \(\hat{\mathbf{g}}\) is the time-varying coefficient \(\hat{a}_{i t}, \hat{b}_{i t}, \hat{s}_{i t}, \hat{h}_{i t}, \hat{r}_{i t}\) and \(\hat{c}_{i t}\) and we have estimation \(\hat{\mathrm{g}}\) with term of K basis function TP1 (t), … ,TPk (t) and t represents the time. In this study, we used Generalized Additive Model (GAM) for the estimation of time-varying coefficient \(\hat{a}_{i t}, \hat{b}_{i t}, \hat{s}_{i t}, \hat{h}_{i t}, \hat{r}_{i t}\) and \(\hat{c}_{i t}\) and used thin-plate splines for basis function TP1 (t), …, TPk (t) because there are no need to choose the knot locations and it performs very well when we have many independent variables (Bringmann et al., 2017; Hongsakulvasu & Liammukda, 2020). The last, we optimal value of estimated time-varying coefficient \(\hat{a}_{i t}, \hat{b}_{i t}, \hat{s}_{i t}, \hat{h}_{i t}, \hat{r}_{i t}\) and \(\hat{c}_{i t}\) can be found when we perform the minimization of this penalized least squares loss function as the following equation
\(\sum_{i=1}^{n}\left\|\varepsilon_{t}\right\|^{2}+\lambda_{w_{m d}}\left(R_{i t}-R f_{t}-\varepsilon_{t}\right)\) (20)
where εt = Rit − Rft − ait − bit (Rm − Rf)t − sitSMBt − hitHMLt − ritRMWt + citCMAt . The last, we are finding a smoothing parameter λ as by using Generalized Cross Validation score (GCV) for optimize equation (20) as the following equation
\(G C V=\frac{T \sum_{t=1}^{T}\left(\widehat{\varepsilon}_{t}\right)^{2}}{[t r(I-A)]^{2}}\) (21)
4. Results and Discussion
4.1. Descriptive Analysis and Stationary Test
For the first analysis, we study by using descriptive analysis for showing a basic information including mean, standard deviation, skewness, and kurtosis of data as the following (Table 2). To check the stationary condition of the data, we perform the Augmented Dickey-Fuller test (ADF test) with 3 equations including 1.no intercept, 2.intercept, and 3.intercept & trend. According to the results of ADF statistics in Table 2, we reject the null hypothesis of nonstationarity, so, we can conclude that all data is stationary.
Table 2: Descriptive statistics and ADF test results.
Notes: Asterisks indicate the rejection of null hypothesis statistical at the 10% (*), 5% (**) or 1% (***) level.
4.2. Time-Varying Coefficient Fama - French Five Factor Model
The results of the time-varying coefficient Fama - French five factor model by using generalized additive model with thin-plate spline are reported in Table 3, Table 4, and Figure 1.
Table 3: Time-varying coefficient Fama - French five factor model results.
Note: The values in the row of at , bt , st , ht , r t , and ct are EDF which refer to the number of basis functions that are used to estimate the timevarying coefficient in the model. Asterisks indicate the rejection of null hypothesis statistical at the 10% (*), 5% (**) or 1% (***) level
Table 4: Timeline of start and end significant time-varying coefficients for the TV-FF5 model.
Figure 1: The estimated Time-varying coefficients \(\hat{a}_{i t}, \hat{b}_{i t}, \hat{s}_{i t}, \hat{h}_{i t}, \hat{r}_{i t},\) and \(\hat{c}_{i t}\) of all portfolios.
According to Table 3. The values in the row of at , bt , st , ht , rt , and ct are Effective Degrees of Freedom (EDF), It refers to the number of basis functions that are used to estimate the time-varying coefficient. If the value of EDF is high, it means that the model uses many basis functions to estimate the time-varying coefficient, so shape of the time-varying coefficient is non-linear and wiggly. On the other hand, if the value of EDF is close to 1, the shape of the time-varying coefficient is linear (Shadish, Zuur, & Sullivan, 2014). In addition, asterisks in Table 4 refer to the rejection of nullhypothesis which means that the time-varying coefficient is significantly different from zero (Wood, 2013).
Figure 1 shows the estimated time-varying coefficients\(\hat{a}_{i t}, \hat{b}_{i t}, \hat{s}_{i t}, \hat{h}_{i t}, \hat{r}_{i t},\)and \(\hat{c}_{i t}\)of all portfolios since July 1990 to April 2020, horizontal dotted lines are crossed with the gray areas (95% confidence interval) which means that the time-varying coefficient is insignificantly different from zero, vertical dotted lines are crossed with the gray areas (95% confidence interval) which means that the timevarying coefficient is start or end of significant time-varying coefficients, and timeline of start and end significant timevarying coefficients are reported in Table 4.
According to Table 3, Table 4, and Figure 1. Timevarying coefficients of intercept (\(\hat{a}_{i t}\) ) are insignificant for all Japan portfolios since July 1990 to April 2020 and the value of EDF close to 1, it means the shape of \(\hat{a}_{t}\) are linearly.
Time-varying coefficients of Rm − Rf ( \(\hat{b}_{t}\) ) are positive significant for all Japan portfolios since July 1990 to April 2020, the value of EDF for SL, SH, BL, and BH portfolio are close to 2 and the value of EDF for SM and BM portfolio are 3.6 and 4.7 respectively, so the shape of ˆ t b for SL, SH, BL, and BH portfolio is close to linearly but the shape of ˆ t b for SM and BM portfolios are nonlinearly.
Time-varying coefficients of SML ( \(\hat{S}_{t}\) ) are positive significant for SL, SM, and SH portfolio and negative significant for BL portfolio since July 1990 to April 2020, the value of EDF for SL, SM, and SH portfolio are 4.6, 3.1, and 6.4 respectively, so the shape of \(\hat{S}_{t}\) for SL, SM, and SH portfolio are nonlinearly, and the value of EDF for BL portfolio is close to 2, so the shape of \(\hat{S}_{t}\) for BL portfolio is close to linearly. \(\hat{S}_{t}\) of BM and BH portfolio are partial significant, \(\hat{S}_{t}\) of BM portfolio is significant since September 1991 to April 2020 and the shape of \(\hat{S}_{t}\) for BM portfolio is close to linearly becuse the value of EDF is 2.2, \(\hat{S}_{t}\) of BH portfolio is positively significant since May 1998 to December 2008 and negative significant since July 1992 to November 1995 and the shape of \(\hat{S}_{t}\) for BH portfolio is nonlinear becuse the value of EDF is 5.9.
Time-varying coefficients of HML ( \(\hat{h}_{t}\) ) are positive significant for SH and BH portfolio and negative significant for SL and BL portfolio since July 1990 to April 2020, the value of EDF for SL, SH, BL, and BH portfolios are 4.2, 4.3, 3.7, and 2.1 respectively, so the shape of \(\hat{h}_{t}\) for SL, SH, and BL portfolio are nonlinearly but the shape of\(\hat{h}_{t}\) for BH portfolio is close to linearly, \(\hat{h}_{t}\) for SH portfolio is positively significant since July 1990 to September 1991 and the shape of \(\hat{h}_{t}\) for SH portfolio is nonlinearly becuse the value of EDF is 4.3, \(\hat{h}_{t}\) for SM portfolio is negatively significant since February 2008 to January 2010 and the shape of \(\hat{h}_{t}\) for SM portfolio is close to linearly becuse the value of EDF is 2.1.
Time-varying coefficient of RMW ( \(\hat{r}_{t}\) ) is positive significant for SM since July 1990 to September 1996 and the shape of\(\hat{r}_{t}\) is close to linearly becuse the value of EDF is 2. For SH portfolio, \(\hat{r}_{t}\) have 2 effect on this portfolio, \(\hat{r}_{t}\) is positive significant since July 1990 to September but January 1994 to April 1996 and February 2008 to January 2010 are negatively significant, and the shape of \(\hat{r}_{t}\) is heavy nonlinearly becuse the value of EDF is 7.8.
Time-varying coefficient of CMA (\(\hat{c}_{t}\) ) are positive significant for SM, SH, and BM portfolios in difference time, \(\hat{c}_{t}\) for SM portfolio is significant since September 1992 to October 2003, \(\hat{c}_{t}\) for SH portfolio is significant since August 1999 to October 2018, and \(\hat{c}_{t}\) for BM portfolio is significant since May 1997 to March 1999, and the value of EDF are 4.9, 2, and 5.2 respectively, so the shape of \(\hat{c}_{t}\) for SM and BM portfolios are nonlinearly but SH portfolio is close to linearly.
5. Conclusions
From the result of the study, we can estimate time-varying coefficients of Fama - French five factor model for explaining the return of Japan portfolio from July 1990 to April 2020. For the time-varying coefficients of intercept are insignificant for all Japan portfolios. The time-varying coefficients of Rm-Rf are positively significant for all Japan portfolios. The timevarying coefficients of SMB are positively significant for SL, SM, SH, and BH portfolio but negative significant for BL, BM, and BH portfolio. The time-varying coefficients of HML are positively significant for SH, BM, and BH portfolio but negatively significant for SL, SM, and BL portfolio. The timevarying coefficients of RMW are positively significant for SM, and SH portfolio but negatively significant for the SH portfolio. The time-varying coefficients of CMA are positively significant for SM, SH, and BM portfolio.
In conclusion, the benefit of time-varying coefficients Fama - French five factor model over than traditional model is that the time-varying coefficients model can capture and show a different effect at different times of 5 factors on Japan portfolios and some factors such as SMB and RMW have a positive and negative effect on portfolios in a different time but the traditional model can’t capture and show a different effect at different times. For developing the model in the next time, we will capture and show a time-varying volatility by plugin Generalized Autoregressive Conditional Heteroscedasticity model (GARCH model) on time-varying coefficients Fama - French five factor model.
References
- Asmarani, S. C., & Wijaya, C. (2020). Effects of Fintech on Stock Return: Evidence from Retail Banks Listed in Indonesia Stock Exchange. Journal of Asian Finance, Economics and Business, 7(7), 95-104. https://doi.org/10.13106/jafeb.2020.vol7.no7.095.
- Bringmann, L. F., Hamaker, E. L., Vigo, D. E., Aubert, A., Borsboom, D., & Tuerlinckx, F. (2017). Changing dynamics: Time-varying autoregressive models using generalized additive modeling. Psychological Methods, 22(3), 409-425. https://doi.org/10.1037/met0000085
- Chen, J. (2018). Market Risk Premium. Retrieved December 22, 2019, from www.investopedia.com/terms/m/marketriskpremium.asp
- Chen, J. (2018). Operating Profit. Retrieved December 22, 2019, from www.investopedia.com/terms/o/operating_profit.asp
- Chen, J. (2018). Portfolio Investment. Retrieved December 22, 2019, from www.investopedia.com/terms/p/portfolio-investment.asp
- Chen, J. (2019). Excess Returns. Retrieved December 22, 2019, from www.investopedia.com/terms/e/excessreturn.asp
- Chen, J. (2019). Risk-Free Rate of Return. Retrieved December 22, 2019, from www.investopedia.com/terms/r/risk-freerate.asp
- Chen, Y. (2017). Lecture 3: MLE and Regression. Retrieved December 22, 2019, from faculty.washington.edu/yenchic/17Sp_403/Lec3_MLE_MSE.pdf
- Chiah, M., Chai, D., Zhong, A., & Li, S. (2016). Better model? An empirical investigation of the Fama-French five-factor model in Australia. International Review of Finance, 16(4), 595-638. https://doi.org/10.1111/irfi.12099
- de la O Gonzalez, M. & Jareno, F. (2019). Testing extensions of Fama & French models: A quantile regression approach. The Quarterly Review of Economics and Finance, 19(71), 188-204.
- Fama, E. F. & Kenneth R. F. (2015). A Five-Factor Asset Pricing Model. Journal of Financial Economics, 15(1), 1-22. https://doi.org/10.1016/j.jfineco.2014.10.010
- Fan, J. & Yao, Q. (2015). The Elements of Financial Econometrics. Cambridge, UK: Cambridge University Press.
- Hayes, A. (2019). Fama and French Three Factor Model. Retrieved December 22, 2019, from www.investopedia.com/terms/f/famaandfrenchthreefactormodel.asp
- Hongsakulvasu, N., & Liammukda, A. (2020). Asian Stock Markets Analysis: The New Evidence from Time-Varying Coefficient Autoregressive Model. Journal of Asian Finance, Economics and Business, 7(9), 95-104. https://doi.org/10.13106/jafeb.2020.vol7.no9.095
- Huang, T. (2019). Is the Fama and French five-factor model robust in the Chinese stock market?. Asia Pacific Management Review, 19(24), 278-289. https://doi.org/10.1016/j.apmrv.2018.10.002
- Jan, M. N., & Ayub, U. (2019). Do the Fama and French Five-Factor Model Forecast Well Using Ann?. Journal of Business Economics and Management, 19(20), 168-191
- Kenton, W. (2019). Small Firm Effect. Retrieved December 22, 2019, from: www.investopedia.com/terms/s/smallfirmeffect.asp
- Kenton, W. (2019). Small Minus Big (SMB). Retrieved December 22, 2019, from: www.investopedia.com/terms/s/small_minus_big.asp
- Kubota, K., & Takehara, H. (2018). Does the Fama and French Five-Factor Model Work Well in Japan? International Review of Finance, 18(1), 137-146. https://doi.org/10.1111/irfi.12126
- Mosoeu, S., & Kodongo, O. (2019). The Fama-French Five-Factor Asset Pricing Model and Emerging Markets Equity Returns. Retrieved from https://papers.ssrn.com/sol3/papers.cfm?abstract_id=3377918.
- Nguyen, D. M. (2016). Fama French five-factor model: Evidence from Vietnam stock market. Master's thesis. University of Vaasa, Vaasa, Finland.
- Shadish, W. R., Zuur, A. F., & Sullivan, K. J. (2014). Using generalized additive (mixed) models to analyze single case designs. Journal of School Psychology, 52(2), 149-178. https://doi.org/10.1016/j.jsp.2013.11.004
- Shaharuddin, S. S., Lau, W., & Ahmad, R. (2018). Is the Fama French Three-Factor Model Relevant? Evidence from Islamic Unit Trust Funds. Journal of Asian Finance, Economics and Business, 5(4), 21-34. http://doi.org/10.13106/jafeb.2018.vol5.no4.21.
- Sharpe, W. F. (1964). Capital Asset Prices: A Theory of Market Equilibrium under Conditions of Risk. The Journal of Finance, 19, 425-442. doi:10.1111/j.1540-6261.1964.tb02865.x.
- Sundqvist, T. (2017). Tests of a Fama-French Five-Factor Asset Pricing Model in the Nordic Stock Markets. Master's thesis, Hanken School of Economics, Finland.
- Wahba, G. (1980). Spline bases, regularization, and generalized cross validation for solving approximation problems with large quantities of noisy data. In: E. Cheney (Ed.), Approximation Theory III. London, UK: Academic Press.
- Wijaya, L. I., Irawan, R. K., & Mahadwartha, P. A. (2018). Test of Fama & French five factor-model on Indonesian stock market. Advances in Social Science, Education and Humanities Research, 18(186), 48-50.
- Wood, S. N. (2003). Thin plate regression splines. Journal of the Royal Statistical Society, Series B, 65, 95-114. https://doi.org/10.1111/1467-9868.00374
- Wood, S. N. (2006). Generalized additive models: An introduction with R. Boca Raton, FL: Chapman and Hall/CRC.
- Wood, S. N. (2013). On p-values for smooth components of an extended generalized additive model. Biometrika, 100(1), 221-228. https://doi.org/10.1093/biomet/ass048
- Zhou, W., & Li, L. (2016). A New Fama-French 5-Factor Model Based on SSAEPD Error and GARCH-Type Volatility. Journal of Mathematical Finance, 16(6), 711-727. https://doi.org/10.4236/jmf.2016.65050
Cited by
- A New Measure of Asset Pricing: Friction-Adjusted Three-Factor Model vol.7, pp.12, 2020, https://doi.org/10.13106/jafeb.2020.vol7.no12.605