Journal of Probability and Statistics

Journal of Probability and Statistics / 2020 / Article

Research Article | Open Access

Volume 2020 |Article ID 1258463 |

Roshani W. Divisekara, Ruwan D. Nawarathna, Lakshika S. Nawarathna, "Forecasting of Global Market Prices of Major Financial Instruments", Journal of Probability and Statistics, vol. 2020, Article ID 1258463, 11 pages, 2020.

Forecasting of Global Market Prices of Major Financial Instruments

Academic Editor: Aera Thavaneswaran
Received23 Jul 2020
Revised26 Aug 2020
Accepted28 Aug 2020
Published14 Sep 2020


One of the easiest and fastest ways of building a healthy financial future is investing in the global market. However, the prices of the global market are highly volatile due to the impact of economic crises. Therefore, future prediction and comparison lead traders to make the low-risk decisions with price. The present study is based on time series modelling to forecast the daily close price values of financial instruments in the global market. The forecasting models were tested with two sample sizes, namely, 5-year close price values for correlation analysis and 3-year close price values for model building from 2013 January to 2018 January. The forecasting capabilities were compared for both ARIMA and GARCH class models, namely, TGARCH, APARCH, and EGARCH. The best-fitting model was selected based on the minimum value of the Akaike information criterion (AIC) and Bayesian information criteria (BIC). Finally, the comparison was carried out between ARIMA and GARCH class models using the measurement of forecast errors, based on the Root Mean Square Deviation (RMSE), Mean Absolute Error (MAE), and Mean absolute percentage error (MAPE). The GARCH model was the best-fitted model for Australian Dollar, Feeder cattle, and Coffee. The APARCH model provides the best out-of-sample performance for Corn and Crude Oil. EGARCH and TGARCH were the better-fitted models for Gold and Treasury bond, respectively. GARCH class models were selected as the better models for forecasting than the ARIMA model for daily close price values in global financial market instruments.

1. Introduction

Recently, there are different methods for investing capital, for instance, investing in gold, investing in foreign currency, current savings, and fix deposits, when compared to the past [1]. In the past, a lot of people were interested to save money in commercial banks for making small interests [2].

In the modern world, lots of investors do not like to save capital in their savings accounts. They are interested in investing money in the global markets to get the maximum returns [2].

Investing in the global market is a simple and speedy method of building a stronger financial investment. The global economic markets are flattering increasingly systematic, and because of this, the competition between computable and traditional investors is warming up and developing modern research, models, and strategies to forecast asset prices. The consignments of knowledge accessible and computers greedy to analyze it are exceptional. Data, technology, and mathematics are now at the spearhead of a financial coup [1].

Presently, the mass investors worldwide started investing grand funds from their capitals. The motivation for investing in the global market is to gain return straightly. Thirty years ago, many companies worldwide mastered exceptional extension and invested mass funds from their capital. It is a durable outlay for companies and individuals. The number of listed companies in the global market has been increased continuously. The universal extension of the market prices and trade volume rates has been modified with hugely unstable oscillations [2].

Investment trading is dominated by several economic circumstances and components. These constituents are influenced by trading intramural and global trading. Sometimes, the market is unstable with enormous oscillations. Variation of the market variance over time is the volatility, and this changes from hugely high and low prices [3, 4].

The time series usage in volatile research in finance and econometrics is not limited to approximation matters, statistical abstractions, and pattern identification. Predominantly, portfolio selection, options trading, and risk management matters in trading have been sort out by these findings. Financial experts and business analysts are interested in taking solutions in an unpredictable situation, so they extremely center of attention to the volatility because it works as a debatable measurement. Recent trading markets are more comparable and desegregated because of globalization growth and technology evolution. The instruction encroachment from each market is strengthening as a result of these evolutions. Experimental works are activated in reactions to these expansions, and guidance communication implements were considered. The discoverers of that study path aimed at the returns sluice consequence between futures and its futures fundamental currency trades over trading’s [5, 6].

Pattern recognition and predicting markets are commonly used in financial trading to estimate the futures market and commodity market. The major mission of financial predicting is to forecast the returns of trading benefits or prominent fluctuations. There are various methods to build models for factors that are affecting trading markets using historical data such as applying recent systems, combining statistical and mathematical hypotheses with economics, and materializing artificial-intelligence techniques. Besides, an association between the futures and futures fundamental currency trading was designated, and primary rates are mainly influenced by the futures prices. Moreover, experimental results illustrate the remarkable telesales relation with regards to pricing facts communication [1].

The motivation in this study is that, in the global market, the prices of instruments are highly fluctuating within a small period. So, uncertainty is high. Since there are uncertain unpredictable fluctuations, there is a high risk. Identifying the factors affecting price changes can predict the habits of price variations. The common computations for forecast cannot used to the global market forecasting because of uncertainty. These global market financial instruments have different returns. Therefore, it should fit separate forecasting models for each financial instrument. Identification of the future forecasts and their behavior can drive to the risk minimization.

The global market financial sector has 51 futures instruments in 8 main sectors. These main sectors are Currencies (CME), Agriculture (CBOT), Energies (NYMEX), Index, Metals, Interest Rates (CBOT), Softs (ICE), and Meats. The currencies sector has 10 futures instruments, the Agriculture sector has 8 futures instruments, the Energies sector has 8 futures instruments, the Index sector has 6 futures instruments, the Metals sector has 6 futures instruments, the Interest Rates sector has 5 futures instruments, the Softs sector has 5 futures instruments, and the Meat sector has 3 futures instruments.

The main motivation of this work is to forecast the global market prices of major financial instruments using Autoregressive Integrated Moving Average (ARIMA), Generalized Autoregressive Conditional Heteroscedasticity (GARCH), Threshold GARCH (TGARCH), Asymmetric Power ARCH (APARCH), and exponential GARCH (EGARCH) models and recognize the relationship between each market [7]. Here, we test the forecasting models with two sample sizes, namely, 5-year daily close price values for correlation analysis and 3-year daily close price values for model building for the past 5-year period from 2013 January to 2018 January. In the beginning, we test the correlations between these 51 major financial instruments to check their behaviors and their relationships. To check the correlations, we used daily close values for the 5-years period from 2013 January to 2018 January. After checking the relationships between markets, we select a few financial instruments and, then, move to build models to predict their futures.

Various types of statistical methods have been dominantly used to discuss the results. They are correlation analysis, descriptive statistical techniques, and time series analysis. These models will be used to build the model and to predict the future market properties. The best model was selected using the lowest AIC and BIC. Then, the out-of-sample, 30-day close price forecast was obtained and compared to the actual close price. Then, we calculate the error values for both ARIMA and GARCH family models. The best model will be identified using accuracy measures, namely, the Root Mean Square Error (RMSE), Mean Absolute Error (MAE), and Mean absolute percentage error (MAPE).

2. Materials and Methods

Historical daily close price values for 7 financial instruments extracted from TradeStation WebAPI (, which is a portal that enables the use of third-party trading applications to access TradeStation’s real-time and historical market data, fast order-execution capabilities, and account and position information, were used in this study. The variables, symbols, and their related sectors are shown in Table 1. Open price, low price, high price, and close price were the four elements of the data. The close price reflects all the activities of the index on a trading day. Hence, the close price was chosen to represent the price of the index to predict.


ADAustralian DollarCurrency
CLCrude oilEnergies
ESES miniIndex
FCFeeder cattleMeats
USTreasury bondInterest rates

First, the preliminary analysis was carried out to understand the patterns and trends of the data. Secondly, the graphical presentation was used to identify the distribution of the markets among each price value. 5-year daily close price values were used for correlation analysis, and 3-year daily close price values were used for model building for the past 5-year period from 2013 January to 2018 January. For one instrument, 1263 observations were used for correlation analysis and 595 observations were used for model building. The correlations between those 51 major financial instruments were tested to check their behaviors and their relationships. High correlations between instruments from the same sectors have appeared. Therefore, one instrument was selected from each sector for further analysis. Then, ARIMA and GARCH models were fitted using past 3-year data, and 30-day future close price values were predicted using fitted models. The best model is identified using the minimum Akaike Information Criterion (AIC) value.

2.1. ARIMA Model

Time series data consists of two basics parts, namely, identifiable pattern, and random noise (error). There are different models in time series including autoregressive (AR), moving average (MA), autoregressive moving average (ARMA), and autoregressive integrated moving average (ARIMA). However, the most commonly used model is the Box–Jenkins ARIMA model that has been successfully applied in economic time series prediction [8]. Moreover, the seasonal time series data have seasonal ARIMA models which are also known as SARIMA. The ARIMA(p,d,q) model is given by the following equation:where is the AR operator of order p, is the MA operator of order q, is the constant term, and is the shock element at time t [9, 10].

2.2. GARCH Model

The standardized residuals can be used for model checking. If the model fits well, the standardized residuals of the GARCH models that fitted to the residuals of ARIMA model data should be plotted. The GARCH model is known as a model of heteroscedasticity, which means it is not constant in variance. The GARCH model is written as the GARCH(q,p) model where q is the number of moving average (MA) terms and p is the number of autoregressive (AR) terms. The GARCH(q,p) model can be represented by the following equation:where is the mean or constant term, is the conditional variance, is the past conditional variance, is the past squared residual return, and [11, 12].

2.3. TGARCH Model

The threshold GARCH (TGARCH) model [13] is given bywhere ε+ = max(ε, 0) and ε = min(ε, 0). α and γ capture the positive and negative effects, respectively.

2.4. APARCH Model

The Asymmetric Power ARCH (APARCH) model [14] is as follows:where ω > 0, ϑ ≥ 0, βj ≥ 0, (j = 1, 2, …, q), αi ≥ 0, and −1 < γi < 1, i = 1, …, p. α and γ recognize the good and bad effects.


Nelson [15] proposed that exponential GARCH (EGARCH) can be given as

The optimal forecasting model was formed by choosing the combination of the forecasting model’s input parameters. Then, the 30-day close price forecast values were compared with the actual close price values. The error values for both models were calculated using the Root Mean Square Deviation (RMSE), Mean Absolute Error (MAE), and Mean Absolute Percentage Error (MAPE). The model which has the lowest MAPE and lowest RMSE values was selected as the best model out of these two models.

To find the best forecasting model for the data, a comparison between fitted ARIMA and GARCH family models was performed using the following steps:(1)It is investigated whether the process is stationary and its variance does not change over time(2)In case that the data were not stationary, they must be converted to stationary ones by taking the log or the difference transformation(3)Then, the ACF, PACF, and EACF were checked for model identification(4)Then, the best model was built, which has the lowest AIC(5)Diagnostic checking for the best model was conducted by verifying the normality of the residuals using the QQ-norm plot and running the Ljung–Box tests [16](6)Finally, the results of the models (ARIMA and GARCH family) were compared through a criterion such as AIC and BIC, and the forecasting performance was tested using RMSE, MASE, and MAE criteria [17, 18]

In summary, ARIMA and linear GARCH class models with three nonlinear GARCH family models, namely, TGARCH, APARCH, and TGARCH, were used to identify the model and forecast the daily close price values. The difference between forecasting GARCH family and ARIMA models was the behavior of the prediction intervals. In times of high volatility, prediction intervals using a GARCH class model widened to consider the higher amount of uncertainty. Similarly, the prediction intervals were narrow in times of lower volatility.

3. Results and Discussion

Figure 1 shows the global market sectors and their correlation groups. There is a strong correlation between the same sectors than the different markets. Therefore, for the analysis, one futures instrument from one financial sector was selected to get more accurate and unbiased results about the global market.

The normality test was applied for data mentioned in Table 1, and all variables were nonnormal. The daily close price data were taken for all financial instruments in the global market during the 3 years from 2015 January to 2018 January.

Table 2 shows the descriptive statistics of daily close price values for eight financial instruments from January 2015 to January 2018. The Minimum value, 1st Quartile, Median, Mean, 2nd Quartile, 3rd Quartile, and Maximum value were checked for selected 8 futures instruments. The contract sizes vary from those of financial instruments. Hence, the relationship between instruments cannot be compared.



According to the summary statistics in Table 2, the average daily close price for AD was 0.7463, while the average daily close value for ES was 2195. Furthermore, the median daily close price value for CL was 54.57, while the median daily close price value for GC was 1296.

3.1. Time Series Analysis

The time series plots of the time series of the daily closing price variables indicate that all values of the autocorrelation function are significantly far from zero and the trend’s ACF is slowly decaying. This implies that there are strong correlations from past values. The stationarity of the time series should be verified. To obtain stationarity data, to remove correlations, and to obtain independent data, a transformation should be applied to the time series [19].

After taking the first differences in the time series of daily close price, the KPSS [20] test was performed. The value of the test was 0.1, which is greater than the significance level of 0.05. Hence, it can be rejected, and it can be concluded that the series is stationary.

3.2. Model Identification

The autocorrelation function (ACF) plot of the first differences for daily close price values was constructed for a variety of lags k = 1, 2, that is, among (Y1, Y1 + k), (Y2, Y2 + k), (Y3, Y3 + k), …, and (Yn − k, Yn), which can identify the order of the ARMA model [21].

The ACF plot of the first difference of daily close price data values was measured for all AD, C, CL, ES, FC, GC, KC, and the US. The trend of the plot was tail-off and cut-off at lag 1, which indicates that the ACF was MA (1).

The plot of the partial autocorrelation function (PACF) of the first difference of daily close price values for the global market estimated the correlation between Yt and Yt − k after removing the effect of the intervening variables Yt − 1, Yt − 2, Yt − 3, …, Yt − k + 1 [21, 22].

3.3. Determining the ARIMA Model Order

The trend of the PACF plot tends to cut off at lag 3 or lag 4 for AD and CL, which implies that the order or the parameters of the partial autocorrelation function were AR (4) or AR (4). The PACF plot tends to cut off at lag 2 or lag 3 for C and FC, which implies that the order or the parameters of the partial autocorrelation function were AR (2) or AR (3). The PACF plot tends to cut off at lag 5 or lag 7 for ES, which implies that the order of the parameters of the partial autocorrelation function were AR (5) or AR (7). The PACF plot tends to cut off at lag 2 or lag 4 for GC, which implies that the order or the parameters of the partial autocorrelation function were AR (2) or AR (4). The PACF plot tends to cut off at lag 3 or lag 11 for KC, which implies that the order or the parameters of the partial autocorrelation function were AR (3) or AR (11), and finally, the PACF plot tends to cut off at lag 2 or lag 6 for US which implies that the order or the parameters of the partial autocorrelation function were AR (2) or AR (6). Mixed compounds of AR and MA models can be used to build many models. The composite models were initially acceptable according to the results of ACF and PACF plots; however, there were criteria to compare fitted models, in the prelude to choosing the best model.

The extended autocorrelation function (EACF) method [23] is an easy graphical tool to identify the orders of the ARMA model. The EACF method uses the fact that if the AR part of a mixed ARMA model is known, the output of the EACF is a two-way table, where the rows correspond to AR order p and the columns to MA order q. Table 3 shows the AIC values of the selected ARIMA models for variables according to the ACF, PACF, and EACF method.


ADARIMA (3,1,1)−4453.01
ARIMA (4,1,1)−4452.11
ARIMA (0,1,1)−4456.04

CARIMA (2,1,1)3737
ARIMA (3,1,1)3737.85
ARIMA (0,1,1)3734.41

CLARIMA (3,1,1)1987.9
ARIMA (4,1,1)1989.6
ARIMA (0,1,2)1984.58
ARIMA (1,1,2)1985.91

ESARIMA (5,1,1)5134.99
ARIMA (7,1,1)5135.28
ARIMA (1,1,1)5130.34
ARIMA (2,1,1)5130.55

FCARIMA (2,1,1)2694.63
ARIMA (3,1,1)2696.58
ARIMA (0,1,1)2691.71
ARIMA (2,1,1)2694.63

GCARIMA (2,1,1)4631.41
ARIMA (4,1,1)4631.11
ARIMA (0,1,1)4629.98
ARIMA (2,1,2)4633.53

KCARIMA (3,1,1)2920.22
ARIMA (1,1,1)2919.97
ARIMA (1,1,0)2918.05

USARIMA (2,1,1)1774.47
ARIMA (6,1,1)1781.38
ARIMA (0,1,1)1770.78

Table 3 exhibits the AIC values of suggested model variables. The best ARIMA model has the minimum value of AIC. Therefore, for AD, the ARIMA (0,1,1) model, for C, the ARIMA (0,1,1) model, for CL, the ARIMA (0,1,2) model, for ES, the ARIMA (1,1,1) model, for FC, the ARIMA (0,1,1) model, for GC, the ARIMA (0,1,1) model, for KC, the ARIMA (1,1,1) model, and for the US, the ARIMA (0,1,1) model were selected.

3.4. Model Estimation

Table 4 shows the estimated parameters for ARIMA models using the maximum likelihood method.


ADARIMA (0,1,1)Θ1 −0.03110.0417

CARIMA (0,1,1)Θ1 −0.00540.0394

CLARIMA (0,1,2)Θ1 −0.02630.0409
Θ2 −0.12980.0406

ESARIMA (1,1,1)Φ1 0.66460.1718
Θ1 −0.72430.1566

FCARIMA (0,1,1)Θ1 0.08300.0427

GCARIMA (0,1,1)Θ1 −0.01380.0388

KCARIMA (1,1,1)Φ1 0.36610.7755
Θ1 −0.35400.7865

USARIMA (0,1,1)Θ1 −0.04300.0402

According to the parameter estimation results in Table 4, the MA parameter for AD was −0.0311 with 0.0417 standard error. The AR and MA parameters for CL were −0.0263 and −0.1298, respectively.

3.5. Diagnostic Checking of the Best ARIMA Model

The next step was to conduct the diagnostic checking for the residuals of the ARIMA models. Model diagnostics were performed by testing the goodness of fit of a model. In this study, the selected ARIMA models were the best model from the suggested models. Therefore, the Box–Pierce and Ljung–Box tests were applied to determine the potential of the model in forecasting the global market’s close price values.

Table 5 shows that the value is higher than 0.05 for all ARIMA models. Hence, it can be concluded that the autocorrelation is different from zero. Therefore, the selected models are appropriate.

Variableχ2Df value


3.6. Summary of Diagnostic Plots

The standardized residuals, the sample ACF of the residuals, and values for the Ljung–Box test statistic were used to check the assumption of independence of error terms. Randomized, nonpattern residuals implied independent errors. The residual plot, ACF, and PACF did not have any significant autocorrelation of any lag, which means that the ARIMA models were appropriated models for variables.

3.7. The Final Model

According to the parameter estimation results in Table 4, the final ARIMA models can be expressed as the following equations.

The final models were ARIMA (0,1,1) for AD, C, FC, GC, and the US. This model can be expressed in the following form:

The final models were ARIMA (1,1,1) for ES and KC. This model can be expressed as follows:

The final model was ARIMA (0,1,2) for CL. This model can be expressed in the following form:

3.8. Forecasting

The main objective of building a model for a time series is forecasting the values for that series at future points of time. The best ARIMA models to represent the series for AD, C, FC, GC, and the US were ARIMA (0,1,1), for ES and KC ARIMA (1,1,1) and, finally, for CL ARIMA (0,1,2).

Figure 2 shows the forecasts for 30 days of close price values for selected instruments. 30-day prediction values were plotted in the blue line, the 80% prediction interval was indicated in the dark gray color area, and the 95% prediction interval was shown in the light gray color area.

3.9. Model Identification

The time series was produced from a white noise series (residual of the ARIMA). Therefore, ACF plots could not be applied to select the orders p and q of the ARIMA model. Akaike Information Criteria (AIC) was used for various combinations of p and q. Then, the model which had the minimum AIC was chosen as the best candidate model. EACF was guided to reduce the options of the best models.

Table 6 indicates the suggested GARCH models from EACF and AIC for variables. Final models were estimated using minimum AIC and BIC values. GARCH (1,1) for AD, GARCH (1,1) for C, GARCH (1,2) for CL, GARCH (1,2) for ES, GARCH (1,1) for FC, GARCH (3,4) for GC, GARCH (1,1) for KC, and GARCH (1,1) for the US were selected using minimum AIC and BIC values.


ADGARCH (1,0)−5.287483−5.257941
GARCH (1,1)−5.287718−5.250792
GARCH (2,1)−5.284379−5.240067

CGARCH (1,0)9.5983069.627847
GARCH (1,1)9.5824169.619342
GARCH (2,1)9.5885089.632819

CLGARCH (1,2)6.1529506.197262
GARCH (2,2)6.1560856.207782
GARCH (3,2)6.1614636.220546

ESGARCH (2,1)12.1335712.17789
GARCH (1,2)12.1334712.17778
GARCH (1,3)12.1385712.19026

FCGARCH (1,0)7.9366717.966212
GARCH (1,1)7.9291587.966084
GARCH (2,1)7.9332217.977533

GCGARCH (3,4)10.3680310.44188
GARCH (6,4)10.3853310.48134
GARCH (3,5)10.3740810.45532

KCGARCH (1,0)7.6730297.702570
GARCH (1,1)7.6647527.701679
GARCH (2,1)7.6756587.719969

USGARCH (1,0)5.8500095.879550
GARCH (1,1)5.8467255.883651
GARCH (2,1)5.8530855.897397

3.10. Lagrange Multiplier (ARCH-LM) Test

The test results presented in Table 7 reject the null hypothesis of no ARCH effect for daily close price values. The tests implied that there was significant volatility clustering in the residual series. Therefore, there was an ARCH effect in the series which indicates that the time series was heteroscedasticitic and volatile [24].

VariableModelLM-ARCH value

ADGARCH (1,1)8.5099650.7441175
CGARCH (1,1)62.78456<0.001
CLGARCH (1,2)12.720920.3896475
ESGARCH (1,2)53.91283<0.001
FCGARCH (1,1)50.21859<0.001
GCGARCH (3,4)15.03660.2394412
KCGARCH (1,1)17.254440.140274
USGARCH (1,1)13.537440.3312158

3.11. Parameter Estimation

Table 8 displays the results of the Box–Ljung test. The values indicated that the models are statistically significant.

VariableModelχ2 value

ADGARCH (1,1)2034<0.001
CGARCH (1,1)2942.5<0.001
CLGARCH (1,2)2814.2<0.001
ESGARCH (1,2)2664.8<0.001
FCGARCH (1,1)3801.4<0.001
GCGARCH (3,4)2723.7<0.001
KCGARCH (1,1)2936.2<0.001
USGARCH (1,1)2936.2<0.001

The parameter estimation of GARCH models is displayed in Table 9. All the parameters were significant for AD, exclude β1 nonsignificant value. Therefore, it was removed from the model. For C, all the parameters were significant. For CL, β1 and β2 nonsignificant were removed from the model. For ES, β1 and β1 nonsignificant were removed from the model. For GC, α2, α3, β1, β2, β3, and β4 nonsignificant were removed from the model. For KC, β1 nonsignificant was removed from the model. For the US, β1 nonsignificant was removed from the model.

VariableModelParametersS.E. value

ADGARCH (1,1)μ 7.553e − 015.748e − 04<0.001
α0 1.893e − 054.816e − 06<0.001
α1 1.000e + 001.368e − 01<0.001
β1 8.723e − 021.025e + 000.395

CGARCH (1,1)μ 470.355700.57851<0.001
α0 9.410343.506900.00729
α1 0.942950.13596<0.001
β1 0.238050.089880.00808

CLGARCH (1,2)μ 51.254410.23806<0.001
α0 0.860550.313800.0061
α1 1.000000.23861<0.001
β1 0.060700.331090.8545
β2 0.050160.166900.7638

ESGARCH (1,2)μ 2.061e + 031.844e + 00<0.001
α0 1.379e + 023.458e + 01<0.001
α1 1.000e + 001.332e − 01<0.001
β1 1.290e − 011.622e − 010.426
β2 2.367e − 029.275e − 020.799

FCGARCH (1,1)μ 146.13260.3324<0.001
α0 2.00450.81870.0144
α1 1.00000.1376<0.001
β1 0.13150.11030.2333

GCGARCH (3,4)μ 1.310e + 032.798e + 00<0.001
α0 9.636e + 012.554e + 010.000162
α1 1.000e + 001.319e − 01<0.001
α2 7.743e − 021.384e − 010.575965
α3 1.000e − 086531e − 021.000000
β1 1.000e − 088.419e − 021.000000
β2 1.000e − 08NANA
β3 1.000e − 08NANA
β4 1.676e − 022.036e − 020.410364

KCGARCH (1,1)μ 166.67490.4603<0.001
α0 4.19711.46020.00405
α1 1.00000.1371<0.001
β1 0.14750.10250.15036

USGARCH (1,1)μ 146.20890.3625<0.001
α0 0.73460.25140.00347
α1 1.00000.1761<0.001
β1 0.12740.14030.36393

3.12. Conditional Variance and Standardized Residuals

Some high values of residuals were recorded. Besides, the model was valid for volatility. The extreme value of the GARCH model was cleared (strong volatility). The increase of conditional variances has corresponded to the rise of volatility in the original series. The standardized residuals of the fitted model were larger values with respect to conditional variances and had a constant mean.

3.13. Model Diagnostics

To check the adequacy of a given time series model, it is common practice to test the significance of the residual autocorrelations. In the GARCH framework, this method is not relevant because the process is always white noise. However, to check the adequacy of a volatility model, the squared residual auto covariance should be invested.

Diagnostic of the adequacy of GARCH models was checked using the plot of the standardized squared residuals. Most values of ACF at successive lags were significantly close to zero which indicates that the models of GARCH were adequate [25].

The value of the Box–Ljung test exceeded 0.05. Therefore, the hypothesis in which the autocorrelation of residuals is different from 0 cannot be rejected, and it implied that the GARCH models were adequate. In Table 9 also, the value of coefficient(s) was significant compared to few that were not significantly greater than 0.05.

3.14. Forecasting

The Ljung–Box statistics and corresponding values were obtained. That indicated no significant correlation at lags 10, 15, and 20 in a squared residual. The value was greater than 0.05, and that implied the model adequately represents the residuals.

3.15. Comparison between ARIMA and GARCH Class Models

The smaller value of the accuracy measurements of forecast errors, that were actual vs. predicted errors RMSE, MAE, and MAPE, were used in choosing the best model among ARIMA and GARCH class models, and results are shown in Table 10.










Table 10 reports the results for an out-of-sample analysis of all models by comparing under three different criteria for four GARCH class models. For the AD, FC, and KC futures, the results support the use of the GARCH model. The APARCH model was the best fit model for the daily close price values of C and CL. The EGARCH and TGARCH were the appropriate models for the GC and US futures, respectively.

3.16. Future Predictions

Table 11 shows the next 30-day average prediction for daily close price values for financial instruments. The next 30-day average for AD was predicted as 0.755.



4. Conclusions

Futures price values are fluctuating due to the impact of many factors. Hence, the traders are interested in forecasting futures price values to obtain optimum marketing decisions and to manage price risk. In this study, ARIMA and GARCH models were used to forecast daily close price values. GARCH models performed better than ARIMA models because of their ability to handle the volatility by the conditional variance. Therefore, the GARCH class models (TGARCH, APARCH, and EGARCH) were used to forecast the daily close price values. For the AD, FC, and KC futures, the results support the use of the GARCH model. The APARCH model was the best fit model for the daily close price values of C and CL. The EGARCH and TGARCH were the appropriate models for the GC and US futures, respectively.

Data Availability

Data are available from the authors upon reasonable request.

Conflicts of Interest

The authors declare that there are no conflicts of interest.


The authors are grateful to Mr. Chandika Jayawardane, Chief Analyst and Managing Director, Global Trade Finance and Quantitative Research, WISEWEL LLC, Kandy, Sri Lanka, for providing the data.


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Copyright © 2020 Roshani W. Divisekara et al. This is an open access article distributed under the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.

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