South Korea 1-Year Real Interest Rate

The 1-year real interest rate is the nominal interest rate adjusted for expected inflation, representing the real cost of borrowing and the real return to saving over a 1-year horizon. It measures the expected purchasing power of the interest payment after accounting for the anticipated erosion of money's value.

Conceptually, the real interest rate is grounded in the Fisher (1930) equation:

where $i$ is the nominal rate, $r$ is the real rate, and $\pi^e$ is expected inflation. The variant used here, the risk-neutral real rate (Definition B), subtracts expected inflation from the ACM risk-neutral yield rather than the market (physical) yield. This removes both the nominal term premium and the inflation risk premium, isolating the pure expectations component, namely the average expected real short rate over the maturity.

This value represents the rate at which the market expects real purchasing power to grow, abstracting from all risk compensation. It corresponds to the physical expectation of the average future real short rate $E^P_t[\bar{r}^{real}_n]$ and is conceptually aligned with the methodology the Federal Reserve Bank of Cleveland uses for its real interest rate estimates (Haubrich, Pennacchi, and Ritchken 2012).

The distinction between ex-ante and ex-post real rates is critical. The ex-ante rate uses model-estimated expected inflation (forward-looking), while the ex-post rate uses realized inflation (backward-looking). Because investment and consumption decisions rest on expectations about future prices rather than on already-observed price changes, only the ex-ante real rate is relevant to those decisions. Mishkin (1981) showed that ex-ante real rates exhibit substantially different time-series properties from ex-post measures, with the gap especially large during periods of inflation surprises.

Two core CPI deflators are provided. The primary (default) uses the DB index (excluding food and energy), aligned with the international standard adopted by the Cleveland Fed, ECB, and OECD. The secondary (hidden) uses the QB index (excluding agricultural products and petroleum), the traditional Korean measure. Both share the same nominal yield and differ only in the expected inflation component.

(1) Risk-Neutral Real Rate Construction. The Definition-B risk-neutral real rate is computed by subtracting the 1-year average expected inflation from the ACM risk-neutral yield:

where $y^{Q,(n)}_t$ is the ACM risk-neutral yield and $\bar{\pi}^{e,(n)}_t$ is the 1-year average expected inflation.

(2) Risk-Neutral Yield Computation. The risk-neutral yield $y^Q$ is computed with $\lambda = 0$ in the ACM affine recursion and equals the average expected path of nominal short rates $E^P_t[\bar{r}_n]$. Subtracting expected inflation removes both the real term premium and the inflation risk premium, leaving only the pure expectations component:

(3) Expected Inflation Estimation. Expected inflation is estimated in three stages, run separately on each core CPI. First, UCSV trend inflation is extracted with a precision-based Gibbs sampler. Second, survey-anchored short-term expectations are estimated by expanding-window OLS combining the BOK Consumer Survey with the UCSV trend. Third, a Nelson-Siegel term structure with $\kappa = 1.0$ maps short-term expectations toward the long-run anchor. The DB-based result (excluding food and energy) is the default, and the QB-based result (excluding agricultural products and petroleum) is the hidden alternative.

(4) Merging and Internal Validation. Because ACM outputs are daily and expected inflation is monthly, the two are merged at monthly frequency. Internal consistency is verified with:

Real interest rates serve as the primary gauge of the restrictiveness or accommodativeness of monetary policy and as a key determinant of intertemporal resource allocation, making them among the most important indicators in macroeconomics (Woodford 2003).

The natural rate of interest ($r^*$), the real rate consistent with output at potential and stable inflation, is the theoretical benchmark against which the observed real rate is evaluated. When the real rate exceeds $r^*$, monetary policy is contractionary; when it falls below $r^*$, policy is expansionary. Laubach and Williams (2003) and Holston, Laubach, and Williams (2017) provide influential estimates of $r^*$ for the U.S. using a state-space model embedded in a small macroeconomic framework, finding a secular decline from roughly 3% in the 1960s to near zero by the 2010s.

This secular decline in real rates across advanced economies has been a defining macroeconomic phenomenon, attributed to demographic shifts including aging populations that reduce investment demand, Summers's (2014) secular stagnation hypothesis emphasizing rising inequality and excess savings, a global savings glut (Bernanke 2005), and declining trend productivity growth. For Korea, Lee and Rhee (2021) estimate that the natural rate has declined from approximately 3% in the early 2000s to around 0.5–1.0% by the 2020s, driven by rapid population aging and a maturing economy.

In the New Keynesian IS curve derived by Clarida, Galí, and Gertler (1999) and Woodford (2003), the output gap depends on the deviation of the real rate from $r^*$:

This theoretical relationship underscores why accurate measurement of the real rate is essential for assessing the policy stance. However, both $r^*$ and expected inflation are unobservable, which complicates measurement in practice.

Real interest rates also play a central role in the international transmission of monetary policy. Under the global financial cycle framework of Rey (2015) and Miranda-Agrippino and Rey (2020), real rate differentials across countries drive cross-border capital flows and asset prices. A significant positive spread between Korean and U.S. real rates may attract foreign capital into KTBs, while a narrowing spread can trigger capital outflows with implications for the won exchange rate and financial stability (Fratzscher 2012).

Real interest rates serve as the fundamental discount rates for valuing assets that generate real cash flows (including equities, real estate, infrastructure, and inflation-linked bonds), making them essential for asset allocation and valuation.

In the Gordon (1962) growth model and its extensions, the equity risk premium is measured relative to the real risk-free rate:

Rising real rates, holding earnings expectations constant, mechanically reduce the present value of future cash flows and exert downward pressure on equity valuations (Hamilton et al. 2016). Campbell and Shiller (1988) formalize this through the dividend-price ratio decomposition, showing that the price-dividend ratio reflects expected future returns, dividend growth, and discount rates, all of which are linked to real rate dynamics.

For bond investors, the real interest rate determines the inflation-adjusted return on nominal fixed income. When real rates are negative, nominal bond holders experience a guaranteed loss of purchasing power, an environment that Ilmanen (2022) describes as 'financial repression,' as seen across many economies during the post-GFC and post-COVID periods. This has important implications for asset allocation, potentially driving investors toward riskier assets in search of positive real returns.

In currencies and international finance, real interest rate differentials are a primary determinant of exchange rate dynamics in the medium term. The real interest rate parity condition implies that persistent real rate differentials should be offset by expected real exchange rate depreciation (Engel 2016). For Korean won investors, tracking the KRW-USD real rate differential provides information about the attractiveness of cross-border fixed income positions after adjusting for inflation differences.

For real estate valuation, the real interest rate sets the opportunity cost of capital for property investment. In Korea's housing market, where household debt levels are elevated, changes in real rates have outsized effects on housing affordability and mortgage debt sustainability, making real rate monitoring essential for both financial stability analysis and household investment decisions.

This is a model-derived series, the output of the Fisher decomposition with the Stock-Watson unobserved-components expected-inflation term structure, so the unit-root reading describes the fitted curve rather than a directly observed price, and the serial-correlation and break diagnostics run on the first difference. The series is tested over its own span from 2000-12-18 to 2026-05-29.

The one-year Treasury real rate is integrated of order one on the level, with the Dickey and Fuller (1979) test in the Said and Dickey (1984) form not rejecting at p = 0.1824, the Phillips and Perron (1988) test concurring at p = 0.1423, and the Kwiatkowski et al. (1992) test rejecting stationarity. On the first difference the Ljung and Box (1978) portmanteau rejects white noise at lags 10 and 20, Q = 47.93 and Q = 95.21 at p = 0.000 and p = 0.000, and the automatic portmanteau of Escanciano and Lobato (2009) concurs with a statistic of 6.84 at p = 0.009. The Bai and Perron (1998, 2003) procedure finds no break in the mean, a reading consistent with the parameter-instability inference of Andrews (1993) on the differenced object (Perron 1989).

This is a daily model output with no low-integer seasonal period, so the seasonal-unit-root and seasonal-stationarity machinery of Hylleberg et al. (1990) and Canova and Hansen (1995) is deliberately not run (Beaulieu and Miron 1992; Ghysels and Osborn 2001).